Predictors of Prolonged Hospitalizations

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Understanding predictors of prolonged hospitalizations among general medicine patients: A guide and preliminary analysis

Hospitalizations frequently last longer than warranted by medical necessity alone, due to inefficiencies within the US healthcare system.[1, 2] Discharge delays place patients at risk for hospital‐acquired complications and increase costs. With the growing emphasis on high‐value care, hospital length of stay (LOS) has emerged as a key metric for inpatient care and will remain a central focus of hospital‐based improvement initiatives for the foreseeable future.

Hospitals may find it difficult to identify the primary drivers of inpatient LOS in a dynamic and increasingly complex healthcare system. Multiple recent policy changes have affected inpatient care. The Health Information Technology for Economic and Clinical Health Act of 2009 has led to widespread adoption of electronic health records (EHRs) that have markedly impacted provider workflows.[3] In October 2013, the Centers for Medicare & Medicaid Services implemented the 2‐midnight rule, which reclassified lower acuity inpatients with an expected stay <48 hours to observation status.[4] In January 2014, expansion of insurance coverage under the Affordable Care Act (ACA) altered payer mix for hospitals nationwide.[5] At a local level, hospitals that are rapidly adjusting resource allocation, capital investments, and marketing efforts and making complex operational decisions (eg, to open new units or change admission or referral algorithms) may simultaneously experience shifts in patient volumes, case‐mix index, and staffing ratios with downstream effects on LOS.

Given the myriad factors influencing inpatient LOS, hospital leaders may encounter real challenges in designing effective LOS reduction strategies. For example, they may expend significant resources on real‐time demand‐capacity management systems to improve hospital‐wide patient flow, but the resultant emphasis on bed placement and early discharges may shave only hours off average LOS.[6, 7] An alternative approach may be to target the small percentage of patients with prolonged hospitalizations who contribute disproportionately to the average LOS, as other initiatives focused on high utilizers have done.[8, 9, 10]

Our institution noted an increase in the average inpatient LOS for general medicine patients from 2012 to 2014, prompting a call to action by hospital leaders. We sought to characterize the predictors of prolonged hospitalizations among medicine patients to guide future efforts aimed at mitigating the contribution of prolonged LOS to overall LOS.

METHODS

Study Design

We performed a retrospective analysis of medicine patients discharged between January 1, 2012 and December 31, 2014, from the University of Colorado Hospital, a 551‐bed urban, quaternary‐care academic medical center in Aurora, Colorado. Patients were included if they were admitted under inpatient status, 18 years of age, and discharged from 1 of our 10 medicine services: 7 services with residents, staffed by hospitalists, general internists, or subspecialists; and 3 services with advanced practice providers, staffed by hospitalists.

Data Collection

We obtained LOS, calendar year of discharge, demographic data, insurance type, discharge disposition, number of medications, consults, intensive care unit (ICU) stays, surgeries (ie, procedures requiring anesthesia), and primary diagnosis by International Classification of Diseases, Ninth Revision codes from an administrative database that had been developed, validated, and maintained by our hospital medicine group. This database was populated with variables from our EHR, which was implemented in September 2011; to minimize variability in data input during the EHR rollout, we excluded data from September 2011 through December 2011. The Colorado Multiple Institutional Review Board reviewed and exempted this database (protocol 13‐2953) as a program evaluation.

Outcomes

We defined a prolonged hospitalization or LOS as >21 days in duration. This represented approximately 2 standard deviations above the mean LOS in our cohort. This cutoff also helped to remove provider‐level variability, as each medicine service was staffed by 2 attendings per month, each working approximately 7 days on and 7 days off. We examined LOS >14 and >30 days in sensitivity analyses to ensure that the selection of >21 days did not impose an arbitrary and invalid limitation on our statistical analysis.

Statistical Analysis

Demographic and clinical data were compared in the group with LOS 21 days versus the group with LOS >21 days with a 2 test for dichotomous variables and Student t test for continuous variables. We then built a multivariable logistic regression model to predict LOS >21 days using the variables that were significantly different between groups in bivariate analyses. A two‐sided P value of <0.05 was considered statistically significant. All data analyses were performed using Stata 12.0 (StataCorp, College Station, TX).

RESULTS

We identified 18,363 inpatient discharges among 12,511 medicine patients between January 1, 2012 and December 31, 2014. Of these discharges, 416 (2.3%) demonstrated prolonged LOS. Prolonged hospitalizations accounted for 18.6% of total inpatient days. The average LOS during the study period was 4.8 days including patients with prolonged LOS and 4.0 days excluding patients with prolonged LOS, a contribution of 0.8 days.

Table 1 compares the characteristics of patients with and without prolonged LOS. Age, insurance, discharge disposition, palliative care consults, ICU stays, and surgeries were among the variables that differed significantly between the 2 groups. Among patients undergoing surgery, those with prolonged LOS were more likely to have surgery >24 hours after admission than those without prolonged LOS (85.7% vs 51.4%, P<0.001).

Baseline Characteristics for Patients With and Without Prolonged Hospitalizations
Variable LOS 21 Days, N=17,947 LOS >21 Days, N=416 P Value
  • NOTE: Abbreviations: ICD‐9, International Classification of Diseases, Ninth Revision; ICU, intensive care unit; LOS, length of stay; LTAC, long‐term acute care; MSSA, methicillin‐sensitive Staphylococcus aureus; MRSA, methicillin‐resistant Staphylococcus aureus; SD, standard deviation. *Top 5 diagnoses for patients with LOS >21 days.

Age, y, mean (SD) 56.4 (18.7) 54.4 (17.1) 0.030
Female 9,256 (52%) 199 (48%) 0.132
Year of discharge <0.001
2012 5,486 (31%) 69 (17%)
2013 6,193 (35%) 162 (39%)
2014 6,268 (35%) 185 (44%)
Race/ethnicity 0.003
White non‐Hispanic 9,702 (54%) 242 (58%)
Black non‐Hispanic 4,000 (22%) 68 (16%)
Hispanic 2,872(16%) 67 (16%)
Asian 578 (3%) 9 (2%)
Other or unknown 795 (4%) 30 (7%)
Language preference 0.795
English 16,049 (89%) 376 (90%)
Spanish 1,052 (6%) 23 (6%)
Other 846 (5%) 17 (4%)
Insurance <0.001
Medicare 5,462 (30%) 109 (26%)
Medicaid 3,406 (19%) 126 (30%)
Dual 2,815 (16%) 64 (15%)
Private 2,714 (15%) 60 (14%)
Indigent/self‐pay 2,829 (16%) 42 (10%)
Other 721 (4%) 15 (4%)
Length of stay, d (SD) 4.0 (3.5) 39.5 (37.3) <0.001
Discharge disposition <0.001
Home with self‐care 13,276 (74%) 115 (28%)
Home with home health 1,584 (9%) 79 (19%)
Hospicehome or inpatient 369 (2%) 19 (5%)
Postacute‐care facility or LTAC 1,761 (10%) 141 (34%)
Expired 113 (1%) 18 (4%)
Other 844 (5%) 44 (11%)
No. of admission medications (SD) 9.7 (7.4) 10.9 (7.8) 0.002
Primary diagnosis by ICD‐9 code*
Sepsis, unspecified 1,548 (9%) 55 (13%) 0.001
Acute respiratory failure 293 (2%) 9 (2%) 0.400
MSSA septicemia 36 (0.2%) 8 (2%) <0.001
MRSA septicemia 13 (0.1%) 7 (2%) <0.001
Alcoholic cirrhosis of the liver 111 (1%) 7 (2%) 0.007
Palliative care consult 398 (2%) 64 (15%) <0.001
ICU stay 2,030 (11%) 246 (59%) <0.001
Surgical procedure 1,800 (10%) 182 (44%) <0.001

Unspecified sepsis was the most frequent primary diagnosis, regardless of LOS category (Table 2). However, the second through fifth most frequent diagnoses differed for patients with and without prolonged LOS.

Top Five Primary Diagnoses for Patients With and Without Prolonged Hospitalizations
N %
  • NOTE: Abbreviations: COPD, chronic obstructive pulmonary disease; LOS, length of stay.

LOS 21 days
1. Sepsis, unspecified 1,548 8.6%
2. Acute pancreatitis 435 2.4%
3. Pneumonia 431 2.4%
4. Acute kidney failure 363 2.0%
5. COPD exacerbation 320 1.8%
LOS >21 days
1. Sepsis, unspecified 55 13.0%
2. Acute respiratory failure 9 2.2%
3. Methicillin‐sensitive Staphylococcus aureus septicemia 8 1.9%
4. Methicillin‐resistant Staphylococcus aureus septicemia 7 1.7%
5. Alcoholic cirrhosis of the liver 7 1.7%

In an adjusted logistic regression model (Table 3), we found lower odds of prolonged LOS for each 10‐year increase in age and higher odds of prolonged LOS for Medicaid insurance, discharge to home with home health, discharge to a postacute‐care or long‐term acute‐care facility, and in‐hospital death. Methicillin‐resistant Staphylococcus aureus (MRSA) septicemia, palliative care consults, ICU stays, and surgeries were all also associated with increased odds of prolonged LOS. We identified a statistically significant interaction between ICU stay and surgical procedure (odds ratio: 2.53, 95% confidence interval: 1.51‐4.26, P<0.001).

Predictors of Prolonged Hospitalizations (LOS >21 Days)*
Outcome: LOS >21 Days Odds Ratio 95% CI P Value
  • NOTE: Abbreviations: CI, confidence interval; ICD‐9, International Classification of Diseases, Ninth Revision; ICU, intensive care unit; LOS, length of stay; LTAC, long‐term acute care; MSSA, methicillin‐sensitive Staphylococcus aureus; MRSA, methicillin‐resistant Staphylococcus aureus. *Clustered by patient.

Age, per 10 years increase in age 0.80 0.73‐0.87 <0.001
Year of discharge
2012 0.47 0.34‐0.67 <0.001
2013 1.10 0.84‐1.43 0.493
2014 Ref
Race/ethnicity
White non‐Hispanic Ref
Black non‐Hispanic 0.89 0.64‐1.22 0.454
Hispanic 1.01 0.70‐1.46 0.952
Asian 0.85 0.40‐1.83 0.679
Other or unknown 1.29 0.73‐2.26 0.378
Insurance
Medicare Ref
Medicaid 1.99 1.29‐3.05 0.002
Dual 1.06 0.72‐1.57 0.765
Private 1.13 0.70‐1.82 0.620
Indigent/self‐pay 1.66 0.95‐2.88 0.073
Other 0.96 0.47‐1.96 0.908
Discharge disposition
Home with self‐care Ref
Home with home health 4.48 3.10‐6.48 <0.001
Hospicehome or inpatient 2.11 0.98‐4.55 0.057
Postacute‐care facility or LTAC 10.37 6.92‐15.56 <0.001
Expired 5.38 2.27‐12.75 <0.001
Other 4.04 2.64‐6.18 <0.001
No. of admission medications 1.00 0.99‐1.02 0.775
Primary diagnosis by ICD‐9 code
Sepsis, unspecified 1.11 0.78‐1.58 0.575
MSSA septicemia 2.44 0.68‐8.67 0.074
MRSA septicemia 8.83 1.72‐45.36 0.009
Alcoholic cirrhosis of the liver 1.25 0.43‐3.65 0.687
Palliative care consult 4.63 2.86‐7.49 <0.001
ICU stay 6.66 5.22‐8.50 <0.001
Surgical procedure 5.04 3.90‐6.52 <0.001

Sensitivity analyses using LOS >14 and >30 days yielded similar results to LOS >21 days (see Supporting Appendix Table 1 in the online version of this article).

DISCUSSION

We found that a small proportion of medicine patients with prolonged hospitalizations contributed substantially to both total inpatient days and average inpatient LOS. Such disproportionate healthcare utilization is concerning in light of the Institute of Medicine's charge for health systems to deliver timely, efficient, and equitable care.[11]

Few studies in the United States have analyzed patient characteristics that predict prolonged LOS, and to our knowledge, none have evaluated prolonged LOS specifically in general medicine patients.[12, 13, 14] Among selected surgical populations, prolonged hospitalizations are most often related to placement difficulties, operational delays, and payer‐related issues, rather than severity of illness, baseline comorbidities, or in‐hospital complications.[12, 13] In our study, we found that patients with prolonged LOS were more likely to require a palliative care consult, ICU stay, or surgery, all proxies for disease severity. Patients with prolonged LOS were also more likely to undergo surgery >24 hours after admission than those without prolonged LOS, suggesting that the former were either too unstable to proceed directly to surgery or developed complications later during their hospitalization. Even after controlling for palliative care consults, ICU stays, and surgeries, placement at a postacute‐care facility was strongly associated with prolonged LOS. Patients with prolonged LOS were also more likely to have Medicaid compared to other insurance types.

Our findings have several potential implications for efforts aimed at decreasing the number of and length of prolonged hospitalizations. Although demographic and clinical factors such as Medicaid insurance, ICU stays, and surgeries are generally not modifiable, they could, particularly in combination, be used to trigger earlier and more intensive case management involvement. A streamlined insurance approval process for Medicaid pending inpatients could be beneficial, given the recent expansion of Medicaid eligibility under the ACA. Hospital partnerships with postacute‐care facilities could also relieve bottlenecks in placement.[8] Chart review of the patients with MRSA septicemia and prolonged LOS indicated that development of an intensive outpatient parenteral antimicrobial therapy pathway with substance abuse counseling could provide an alternative to extended inpatient treatment for intravenous drug users with complicated infections.[15]

This study has several limitations. First, given the lack of consensus in the literature regarding the definition of a prolonged hospitalization, it is difficult to directly compare our results with existing studies.[8, 12, 13, 14] However, we believe LOS >21 days to be a meaningful cutoff for our cohort. Most demographic and clinical variables that were predictive at >21 days were also predictive at >14 and >30 days, which reassured us that the relationship between variables and prolonged LOS was stable at different thresholds. Second, our database did not allow us to fully adjust for baseline comorbidities or categorize the reasons for discharge delays. Finally, this was a single‐center program evaluation. Although this limits generalization to other institutions, we believe our approach may serve as a guide for others interested in reducing prolonged hospitalizations.

In summary, prolonged hospitalizations represent a potentially high‐yield target for LOS reduction efforts. Prolonged hospitalizations among medicine patients at our institution particularly affected Medicaid enrollees with complex hospital stays who were not discharged home. Further studies are needed to determine the specific reasons for unnecessary hospital days in this population.

Acknowledgements

The authors thank Essey Yirdaw for her contributions to the building and management of the database that informed this work.

Disclosure: M.E.A. conceived of the study concept and design and drafted the manuscript. J.J.G. assisted with the study design and made critical revisions to the final manuscript. D.A., R.P., and R.C. assisted with the study design and made critical revisions to the manuscript. C.D.J. assisted with the study design, performed data analyses, and made critical revisions to the manuscript. RC has disclosed that her time is funded by a National Institutes of Health grant unrelated to this study. A modified abstract was presented in poster format at the Society of Hospital Medicine Research, Innovations, and Vignettes Competition 2015 Annual Meeting, held March 29 April 1, 2015, in National Harbor, Maryland. The authors have no conflicts of interest to disclose.

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References
  1. Kim CS, Hart AL, Paretti RF, et al. Excess hospitalization days in an academic medical center: perceptions of hospitalists and discharge planners. Am J Manag Care. 2011;17(2):e34e42.
  2. Carey MR, Sheth H, Braithwaite RS. A prospective study of reasons for prolonged hospitalizations on a general medicine teaching service. J Gen Intern Med. 2005;20(2):108115.
  3. DesRoches CM, Charles D, Furukawa MF, et al. Adoption of electronic health records grows rapidly, but fewer than half of U.S. hospitals had at least a basic system in 2012. Health Aff (Millwood). 2013;32(8):14781485.
  4. Sheehy AM, Caponi B, Gangireddy S, et al. Observation and inpatient status: clinical impact of the 2‐midnight rule. J Hosp Med. 2014;9(4):203209.
  5. DeLeire T, Joynt K, McDonald R. Impact of insurance expansion on hospital uncompensated care costs in 2014. Department of Health and Human Services Office of the Assistant Secretary for Planning and Evaluation. Available at: http://aspe.hhs.gov/health/reports/2014/uncompensatedcare/ib_uncompensatedcare.pdf. Accessed March 28, 2015.
  6. Resar R, Nolan K, Kaczynski D, Jensen K. Using real‐time demand capacity management to improve hospital‐wide patient flow. Jt Comm J Qual Patient Saf. 2011;37(5):217227.
  7. Chen LM, Freitag MH, Franco M, Sullivan CD, Dickson C, Brancati FL. Natural history of late discharges from a general medical ward. J Hosp Med. 2009;4(4):226233.
  8. Lagoe R, Pernisi L, Luziani M, Littau S. Addressing hospital length of stay outlier patients: a community‐wide approach. Adv Biosci Biotechol. 2014;5:188196.
  9. Milstein A, Gilbertson E. American medical home runs. Health Aff (Millwood). 2009;28(5):13171326.
  10. Gawande A. The hot spotters: can we lower medical costs by giving the neediest patients better care? New Yorker. January 2011:4051.
  11. Institute of Medicine. Crossing the Quality Chasm. Washington, DC: National Academies Press; 2001.
  12. Hwabejire JO, Kaafarani HM, Imam AM, et al. Excessively long hospital stays after trauma are not related to the severity of illness: let's aim to the right target! JAMA Surg. 2013;148(1):956961.
  13. Krell RW, Girotti ME, Dimick JB. Extended length of stay after surgery: complications, inefficient practice, or sick patients? JAMA Surg. 2014;149(8):815820.
  14. Foer D, Ornstein K, Soriano TA, Kathuria N, Dunn A. Nonmedical factors associated with prolonged hospital length of stay in an urban homebound population. J Hosp Med. 2012;7(2):7378.
  15. Ho J, Archuleta S, Sulaiman Z, Fisher D. Safe and successful treatment of intravenous drug users with a peripherally inserted central catheter in an outpatient parenteral antibiotic treatment service. J Antimicrob Chemother. 2010;65(12):26412644.
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Hospitalizations frequently last longer than warranted by medical necessity alone, due to inefficiencies within the US healthcare system.[1, 2] Discharge delays place patients at risk for hospital‐acquired complications and increase costs. With the growing emphasis on high‐value care, hospital length of stay (LOS) has emerged as a key metric for inpatient care and will remain a central focus of hospital‐based improvement initiatives for the foreseeable future.

Hospitals may find it difficult to identify the primary drivers of inpatient LOS in a dynamic and increasingly complex healthcare system. Multiple recent policy changes have affected inpatient care. The Health Information Technology for Economic and Clinical Health Act of 2009 has led to widespread adoption of electronic health records (EHRs) that have markedly impacted provider workflows.[3] In October 2013, the Centers for Medicare & Medicaid Services implemented the 2‐midnight rule, which reclassified lower acuity inpatients with an expected stay <48 hours to observation status.[4] In January 2014, expansion of insurance coverage under the Affordable Care Act (ACA) altered payer mix for hospitals nationwide.[5] At a local level, hospitals that are rapidly adjusting resource allocation, capital investments, and marketing efforts and making complex operational decisions (eg, to open new units or change admission or referral algorithms) may simultaneously experience shifts in patient volumes, case‐mix index, and staffing ratios with downstream effects on LOS.

Given the myriad factors influencing inpatient LOS, hospital leaders may encounter real challenges in designing effective LOS reduction strategies. For example, they may expend significant resources on real‐time demand‐capacity management systems to improve hospital‐wide patient flow, but the resultant emphasis on bed placement and early discharges may shave only hours off average LOS.[6, 7] An alternative approach may be to target the small percentage of patients with prolonged hospitalizations who contribute disproportionately to the average LOS, as other initiatives focused on high utilizers have done.[8, 9, 10]

Our institution noted an increase in the average inpatient LOS for general medicine patients from 2012 to 2014, prompting a call to action by hospital leaders. We sought to characterize the predictors of prolonged hospitalizations among medicine patients to guide future efforts aimed at mitigating the contribution of prolonged LOS to overall LOS.

METHODS

Study Design

We performed a retrospective analysis of medicine patients discharged between January 1, 2012 and December 31, 2014, from the University of Colorado Hospital, a 551‐bed urban, quaternary‐care academic medical center in Aurora, Colorado. Patients were included if they were admitted under inpatient status, 18 years of age, and discharged from 1 of our 10 medicine services: 7 services with residents, staffed by hospitalists, general internists, or subspecialists; and 3 services with advanced practice providers, staffed by hospitalists.

Data Collection

We obtained LOS, calendar year of discharge, demographic data, insurance type, discharge disposition, number of medications, consults, intensive care unit (ICU) stays, surgeries (ie, procedures requiring anesthesia), and primary diagnosis by International Classification of Diseases, Ninth Revision codes from an administrative database that had been developed, validated, and maintained by our hospital medicine group. This database was populated with variables from our EHR, which was implemented in September 2011; to minimize variability in data input during the EHR rollout, we excluded data from September 2011 through December 2011. The Colorado Multiple Institutional Review Board reviewed and exempted this database (protocol 13‐2953) as a program evaluation.

Outcomes

We defined a prolonged hospitalization or LOS as >21 days in duration. This represented approximately 2 standard deviations above the mean LOS in our cohort. This cutoff also helped to remove provider‐level variability, as each medicine service was staffed by 2 attendings per month, each working approximately 7 days on and 7 days off. We examined LOS >14 and >30 days in sensitivity analyses to ensure that the selection of >21 days did not impose an arbitrary and invalid limitation on our statistical analysis.

Statistical Analysis

Demographic and clinical data were compared in the group with LOS 21 days versus the group with LOS >21 days with a 2 test for dichotomous variables and Student t test for continuous variables. We then built a multivariable logistic regression model to predict LOS >21 days using the variables that were significantly different between groups in bivariate analyses. A two‐sided P value of <0.05 was considered statistically significant. All data analyses were performed using Stata 12.0 (StataCorp, College Station, TX).

RESULTS

We identified 18,363 inpatient discharges among 12,511 medicine patients between January 1, 2012 and December 31, 2014. Of these discharges, 416 (2.3%) demonstrated prolonged LOS. Prolonged hospitalizations accounted for 18.6% of total inpatient days. The average LOS during the study period was 4.8 days including patients with prolonged LOS and 4.0 days excluding patients with prolonged LOS, a contribution of 0.8 days.

Table 1 compares the characteristics of patients with and without prolonged LOS. Age, insurance, discharge disposition, palliative care consults, ICU stays, and surgeries were among the variables that differed significantly between the 2 groups. Among patients undergoing surgery, those with prolonged LOS were more likely to have surgery >24 hours after admission than those without prolonged LOS (85.7% vs 51.4%, P<0.001).

Baseline Characteristics for Patients With and Without Prolonged Hospitalizations
Variable LOS 21 Days, N=17,947 LOS >21 Days, N=416 P Value
  • NOTE: Abbreviations: ICD‐9, International Classification of Diseases, Ninth Revision; ICU, intensive care unit; LOS, length of stay; LTAC, long‐term acute care; MSSA, methicillin‐sensitive Staphylococcus aureus; MRSA, methicillin‐resistant Staphylococcus aureus; SD, standard deviation. *Top 5 diagnoses for patients with LOS >21 days.

Age, y, mean (SD) 56.4 (18.7) 54.4 (17.1) 0.030
Female 9,256 (52%) 199 (48%) 0.132
Year of discharge <0.001
2012 5,486 (31%) 69 (17%)
2013 6,193 (35%) 162 (39%)
2014 6,268 (35%) 185 (44%)
Race/ethnicity 0.003
White non‐Hispanic 9,702 (54%) 242 (58%)
Black non‐Hispanic 4,000 (22%) 68 (16%)
Hispanic 2,872(16%) 67 (16%)
Asian 578 (3%) 9 (2%)
Other or unknown 795 (4%) 30 (7%)
Language preference 0.795
English 16,049 (89%) 376 (90%)
Spanish 1,052 (6%) 23 (6%)
Other 846 (5%) 17 (4%)
Insurance <0.001
Medicare 5,462 (30%) 109 (26%)
Medicaid 3,406 (19%) 126 (30%)
Dual 2,815 (16%) 64 (15%)
Private 2,714 (15%) 60 (14%)
Indigent/self‐pay 2,829 (16%) 42 (10%)
Other 721 (4%) 15 (4%)
Length of stay, d (SD) 4.0 (3.5) 39.5 (37.3) <0.001
Discharge disposition <0.001
Home with self‐care 13,276 (74%) 115 (28%)
Home with home health 1,584 (9%) 79 (19%)
Hospicehome or inpatient 369 (2%) 19 (5%)
Postacute‐care facility or LTAC 1,761 (10%) 141 (34%)
Expired 113 (1%) 18 (4%)
Other 844 (5%) 44 (11%)
No. of admission medications (SD) 9.7 (7.4) 10.9 (7.8) 0.002
Primary diagnosis by ICD‐9 code*
Sepsis, unspecified 1,548 (9%) 55 (13%) 0.001
Acute respiratory failure 293 (2%) 9 (2%) 0.400
MSSA septicemia 36 (0.2%) 8 (2%) <0.001
MRSA septicemia 13 (0.1%) 7 (2%) <0.001
Alcoholic cirrhosis of the liver 111 (1%) 7 (2%) 0.007
Palliative care consult 398 (2%) 64 (15%) <0.001
ICU stay 2,030 (11%) 246 (59%) <0.001
Surgical procedure 1,800 (10%) 182 (44%) <0.001

Unspecified sepsis was the most frequent primary diagnosis, regardless of LOS category (Table 2). However, the second through fifth most frequent diagnoses differed for patients with and without prolonged LOS.

Top Five Primary Diagnoses for Patients With and Without Prolonged Hospitalizations
N %
  • NOTE: Abbreviations: COPD, chronic obstructive pulmonary disease; LOS, length of stay.

LOS 21 days
1. Sepsis, unspecified 1,548 8.6%
2. Acute pancreatitis 435 2.4%
3. Pneumonia 431 2.4%
4. Acute kidney failure 363 2.0%
5. COPD exacerbation 320 1.8%
LOS >21 days
1. Sepsis, unspecified 55 13.0%
2. Acute respiratory failure 9 2.2%
3. Methicillin‐sensitive Staphylococcus aureus septicemia 8 1.9%
4. Methicillin‐resistant Staphylococcus aureus septicemia 7 1.7%
5. Alcoholic cirrhosis of the liver 7 1.7%

In an adjusted logistic regression model (Table 3), we found lower odds of prolonged LOS for each 10‐year increase in age and higher odds of prolonged LOS for Medicaid insurance, discharge to home with home health, discharge to a postacute‐care or long‐term acute‐care facility, and in‐hospital death. Methicillin‐resistant Staphylococcus aureus (MRSA) septicemia, palliative care consults, ICU stays, and surgeries were all also associated with increased odds of prolonged LOS. We identified a statistically significant interaction between ICU stay and surgical procedure (odds ratio: 2.53, 95% confidence interval: 1.51‐4.26, P<0.001).

Predictors of Prolonged Hospitalizations (LOS >21 Days)*
Outcome: LOS >21 Days Odds Ratio 95% CI P Value
  • NOTE: Abbreviations: CI, confidence interval; ICD‐9, International Classification of Diseases, Ninth Revision; ICU, intensive care unit; LOS, length of stay; LTAC, long‐term acute care; MSSA, methicillin‐sensitive Staphylococcus aureus; MRSA, methicillin‐resistant Staphylococcus aureus. *Clustered by patient.

Age, per 10 years increase in age 0.80 0.73‐0.87 <0.001
Year of discharge
2012 0.47 0.34‐0.67 <0.001
2013 1.10 0.84‐1.43 0.493
2014 Ref
Race/ethnicity
White non‐Hispanic Ref
Black non‐Hispanic 0.89 0.64‐1.22 0.454
Hispanic 1.01 0.70‐1.46 0.952
Asian 0.85 0.40‐1.83 0.679
Other or unknown 1.29 0.73‐2.26 0.378
Insurance
Medicare Ref
Medicaid 1.99 1.29‐3.05 0.002
Dual 1.06 0.72‐1.57 0.765
Private 1.13 0.70‐1.82 0.620
Indigent/self‐pay 1.66 0.95‐2.88 0.073
Other 0.96 0.47‐1.96 0.908
Discharge disposition
Home with self‐care Ref
Home with home health 4.48 3.10‐6.48 <0.001
Hospicehome or inpatient 2.11 0.98‐4.55 0.057
Postacute‐care facility or LTAC 10.37 6.92‐15.56 <0.001
Expired 5.38 2.27‐12.75 <0.001
Other 4.04 2.64‐6.18 <0.001
No. of admission medications 1.00 0.99‐1.02 0.775
Primary diagnosis by ICD‐9 code
Sepsis, unspecified 1.11 0.78‐1.58 0.575
MSSA septicemia 2.44 0.68‐8.67 0.074
MRSA septicemia 8.83 1.72‐45.36 0.009
Alcoholic cirrhosis of the liver 1.25 0.43‐3.65 0.687
Palliative care consult 4.63 2.86‐7.49 <0.001
ICU stay 6.66 5.22‐8.50 <0.001
Surgical procedure 5.04 3.90‐6.52 <0.001

Sensitivity analyses using LOS >14 and >30 days yielded similar results to LOS >21 days (see Supporting Appendix Table 1 in the online version of this article).

DISCUSSION

We found that a small proportion of medicine patients with prolonged hospitalizations contributed substantially to both total inpatient days and average inpatient LOS. Such disproportionate healthcare utilization is concerning in light of the Institute of Medicine's charge for health systems to deliver timely, efficient, and equitable care.[11]

Few studies in the United States have analyzed patient characteristics that predict prolonged LOS, and to our knowledge, none have evaluated prolonged LOS specifically in general medicine patients.[12, 13, 14] Among selected surgical populations, prolonged hospitalizations are most often related to placement difficulties, operational delays, and payer‐related issues, rather than severity of illness, baseline comorbidities, or in‐hospital complications.[12, 13] In our study, we found that patients with prolonged LOS were more likely to require a palliative care consult, ICU stay, or surgery, all proxies for disease severity. Patients with prolonged LOS were also more likely to undergo surgery >24 hours after admission than those without prolonged LOS, suggesting that the former were either too unstable to proceed directly to surgery or developed complications later during their hospitalization. Even after controlling for palliative care consults, ICU stays, and surgeries, placement at a postacute‐care facility was strongly associated with prolonged LOS. Patients with prolonged LOS were also more likely to have Medicaid compared to other insurance types.

Our findings have several potential implications for efforts aimed at decreasing the number of and length of prolonged hospitalizations. Although demographic and clinical factors such as Medicaid insurance, ICU stays, and surgeries are generally not modifiable, they could, particularly in combination, be used to trigger earlier and more intensive case management involvement. A streamlined insurance approval process for Medicaid pending inpatients could be beneficial, given the recent expansion of Medicaid eligibility under the ACA. Hospital partnerships with postacute‐care facilities could also relieve bottlenecks in placement.[8] Chart review of the patients with MRSA septicemia and prolonged LOS indicated that development of an intensive outpatient parenteral antimicrobial therapy pathway with substance abuse counseling could provide an alternative to extended inpatient treatment for intravenous drug users with complicated infections.[15]

This study has several limitations. First, given the lack of consensus in the literature regarding the definition of a prolonged hospitalization, it is difficult to directly compare our results with existing studies.[8, 12, 13, 14] However, we believe LOS >21 days to be a meaningful cutoff for our cohort. Most demographic and clinical variables that were predictive at >21 days were also predictive at >14 and >30 days, which reassured us that the relationship between variables and prolonged LOS was stable at different thresholds. Second, our database did not allow us to fully adjust for baseline comorbidities or categorize the reasons for discharge delays. Finally, this was a single‐center program evaluation. Although this limits generalization to other institutions, we believe our approach may serve as a guide for others interested in reducing prolonged hospitalizations.

In summary, prolonged hospitalizations represent a potentially high‐yield target for LOS reduction efforts. Prolonged hospitalizations among medicine patients at our institution particularly affected Medicaid enrollees with complex hospital stays who were not discharged home. Further studies are needed to determine the specific reasons for unnecessary hospital days in this population.

Acknowledgements

The authors thank Essey Yirdaw for her contributions to the building and management of the database that informed this work.

Disclosure: M.E.A. conceived of the study concept and design and drafted the manuscript. J.J.G. assisted with the study design and made critical revisions to the final manuscript. D.A., R.P., and R.C. assisted with the study design and made critical revisions to the manuscript. C.D.J. assisted with the study design, performed data analyses, and made critical revisions to the manuscript. RC has disclosed that her time is funded by a National Institutes of Health grant unrelated to this study. A modified abstract was presented in poster format at the Society of Hospital Medicine Research, Innovations, and Vignettes Competition 2015 Annual Meeting, held March 29 April 1, 2015, in National Harbor, Maryland. The authors have no conflicts of interest to disclose.

Hospitalizations frequently last longer than warranted by medical necessity alone, due to inefficiencies within the US healthcare system.[1, 2] Discharge delays place patients at risk for hospital‐acquired complications and increase costs. With the growing emphasis on high‐value care, hospital length of stay (LOS) has emerged as a key metric for inpatient care and will remain a central focus of hospital‐based improvement initiatives for the foreseeable future.

Hospitals may find it difficult to identify the primary drivers of inpatient LOS in a dynamic and increasingly complex healthcare system. Multiple recent policy changes have affected inpatient care. The Health Information Technology for Economic and Clinical Health Act of 2009 has led to widespread adoption of electronic health records (EHRs) that have markedly impacted provider workflows.[3] In October 2013, the Centers for Medicare & Medicaid Services implemented the 2‐midnight rule, which reclassified lower acuity inpatients with an expected stay <48 hours to observation status.[4] In January 2014, expansion of insurance coverage under the Affordable Care Act (ACA) altered payer mix for hospitals nationwide.[5] At a local level, hospitals that are rapidly adjusting resource allocation, capital investments, and marketing efforts and making complex operational decisions (eg, to open new units or change admission or referral algorithms) may simultaneously experience shifts in patient volumes, case‐mix index, and staffing ratios with downstream effects on LOS.

Given the myriad factors influencing inpatient LOS, hospital leaders may encounter real challenges in designing effective LOS reduction strategies. For example, they may expend significant resources on real‐time demand‐capacity management systems to improve hospital‐wide patient flow, but the resultant emphasis on bed placement and early discharges may shave only hours off average LOS.[6, 7] An alternative approach may be to target the small percentage of patients with prolonged hospitalizations who contribute disproportionately to the average LOS, as other initiatives focused on high utilizers have done.[8, 9, 10]

Our institution noted an increase in the average inpatient LOS for general medicine patients from 2012 to 2014, prompting a call to action by hospital leaders. We sought to characterize the predictors of prolonged hospitalizations among medicine patients to guide future efforts aimed at mitigating the contribution of prolonged LOS to overall LOS.

METHODS

Study Design

We performed a retrospective analysis of medicine patients discharged between January 1, 2012 and December 31, 2014, from the University of Colorado Hospital, a 551‐bed urban, quaternary‐care academic medical center in Aurora, Colorado. Patients were included if they were admitted under inpatient status, 18 years of age, and discharged from 1 of our 10 medicine services: 7 services with residents, staffed by hospitalists, general internists, or subspecialists; and 3 services with advanced practice providers, staffed by hospitalists.

Data Collection

We obtained LOS, calendar year of discharge, demographic data, insurance type, discharge disposition, number of medications, consults, intensive care unit (ICU) stays, surgeries (ie, procedures requiring anesthesia), and primary diagnosis by International Classification of Diseases, Ninth Revision codes from an administrative database that had been developed, validated, and maintained by our hospital medicine group. This database was populated with variables from our EHR, which was implemented in September 2011; to minimize variability in data input during the EHR rollout, we excluded data from September 2011 through December 2011. The Colorado Multiple Institutional Review Board reviewed and exempted this database (protocol 13‐2953) as a program evaluation.

Outcomes

We defined a prolonged hospitalization or LOS as >21 days in duration. This represented approximately 2 standard deviations above the mean LOS in our cohort. This cutoff also helped to remove provider‐level variability, as each medicine service was staffed by 2 attendings per month, each working approximately 7 days on and 7 days off. We examined LOS >14 and >30 days in sensitivity analyses to ensure that the selection of >21 days did not impose an arbitrary and invalid limitation on our statistical analysis.

Statistical Analysis

Demographic and clinical data were compared in the group with LOS 21 days versus the group with LOS >21 days with a 2 test for dichotomous variables and Student t test for continuous variables. We then built a multivariable logistic regression model to predict LOS >21 days using the variables that were significantly different between groups in bivariate analyses. A two‐sided P value of <0.05 was considered statistically significant. All data analyses were performed using Stata 12.0 (StataCorp, College Station, TX).

RESULTS

We identified 18,363 inpatient discharges among 12,511 medicine patients between January 1, 2012 and December 31, 2014. Of these discharges, 416 (2.3%) demonstrated prolonged LOS. Prolonged hospitalizations accounted for 18.6% of total inpatient days. The average LOS during the study period was 4.8 days including patients with prolonged LOS and 4.0 days excluding patients with prolonged LOS, a contribution of 0.8 days.

Table 1 compares the characteristics of patients with and without prolonged LOS. Age, insurance, discharge disposition, palliative care consults, ICU stays, and surgeries were among the variables that differed significantly between the 2 groups. Among patients undergoing surgery, those with prolonged LOS were more likely to have surgery >24 hours after admission than those without prolonged LOS (85.7% vs 51.4%, P<0.001).

Baseline Characteristics for Patients With and Without Prolonged Hospitalizations
Variable LOS 21 Days, N=17,947 LOS >21 Days, N=416 P Value
  • NOTE: Abbreviations: ICD‐9, International Classification of Diseases, Ninth Revision; ICU, intensive care unit; LOS, length of stay; LTAC, long‐term acute care; MSSA, methicillin‐sensitive Staphylococcus aureus; MRSA, methicillin‐resistant Staphylococcus aureus; SD, standard deviation. *Top 5 diagnoses for patients with LOS >21 days.

Age, y, mean (SD) 56.4 (18.7) 54.4 (17.1) 0.030
Female 9,256 (52%) 199 (48%) 0.132
Year of discharge <0.001
2012 5,486 (31%) 69 (17%)
2013 6,193 (35%) 162 (39%)
2014 6,268 (35%) 185 (44%)
Race/ethnicity 0.003
White non‐Hispanic 9,702 (54%) 242 (58%)
Black non‐Hispanic 4,000 (22%) 68 (16%)
Hispanic 2,872(16%) 67 (16%)
Asian 578 (3%) 9 (2%)
Other or unknown 795 (4%) 30 (7%)
Language preference 0.795
English 16,049 (89%) 376 (90%)
Spanish 1,052 (6%) 23 (6%)
Other 846 (5%) 17 (4%)
Insurance <0.001
Medicare 5,462 (30%) 109 (26%)
Medicaid 3,406 (19%) 126 (30%)
Dual 2,815 (16%) 64 (15%)
Private 2,714 (15%) 60 (14%)
Indigent/self‐pay 2,829 (16%) 42 (10%)
Other 721 (4%) 15 (4%)
Length of stay, d (SD) 4.0 (3.5) 39.5 (37.3) <0.001
Discharge disposition <0.001
Home with self‐care 13,276 (74%) 115 (28%)
Home with home health 1,584 (9%) 79 (19%)
Hospicehome or inpatient 369 (2%) 19 (5%)
Postacute‐care facility or LTAC 1,761 (10%) 141 (34%)
Expired 113 (1%) 18 (4%)
Other 844 (5%) 44 (11%)
No. of admission medications (SD) 9.7 (7.4) 10.9 (7.8) 0.002
Primary diagnosis by ICD‐9 code*
Sepsis, unspecified 1,548 (9%) 55 (13%) 0.001
Acute respiratory failure 293 (2%) 9 (2%) 0.400
MSSA septicemia 36 (0.2%) 8 (2%) <0.001
MRSA septicemia 13 (0.1%) 7 (2%) <0.001
Alcoholic cirrhosis of the liver 111 (1%) 7 (2%) 0.007
Palliative care consult 398 (2%) 64 (15%) <0.001
ICU stay 2,030 (11%) 246 (59%) <0.001
Surgical procedure 1,800 (10%) 182 (44%) <0.001

Unspecified sepsis was the most frequent primary diagnosis, regardless of LOS category (Table 2). However, the second through fifth most frequent diagnoses differed for patients with and without prolonged LOS.

Top Five Primary Diagnoses for Patients With and Without Prolonged Hospitalizations
N %
  • NOTE: Abbreviations: COPD, chronic obstructive pulmonary disease; LOS, length of stay.

LOS 21 days
1. Sepsis, unspecified 1,548 8.6%
2. Acute pancreatitis 435 2.4%
3. Pneumonia 431 2.4%
4. Acute kidney failure 363 2.0%
5. COPD exacerbation 320 1.8%
LOS >21 days
1. Sepsis, unspecified 55 13.0%
2. Acute respiratory failure 9 2.2%
3. Methicillin‐sensitive Staphylococcus aureus septicemia 8 1.9%
4. Methicillin‐resistant Staphylococcus aureus septicemia 7 1.7%
5. Alcoholic cirrhosis of the liver 7 1.7%

In an adjusted logistic regression model (Table 3), we found lower odds of prolonged LOS for each 10‐year increase in age and higher odds of prolonged LOS for Medicaid insurance, discharge to home with home health, discharge to a postacute‐care or long‐term acute‐care facility, and in‐hospital death. Methicillin‐resistant Staphylococcus aureus (MRSA) septicemia, palliative care consults, ICU stays, and surgeries were all also associated with increased odds of prolonged LOS. We identified a statistically significant interaction between ICU stay and surgical procedure (odds ratio: 2.53, 95% confidence interval: 1.51‐4.26, P<0.001).

Predictors of Prolonged Hospitalizations (LOS >21 Days)*
Outcome: LOS >21 Days Odds Ratio 95% CI P Value
  • NOTE: Abbreviations: CI, confidence interval; ICD‐9, International Classification of Diseases, Ninth Revision; ICU, intensive care unit; LOS, length of stay; LTAC, long‐term acute care; MSSA, methicillin‐sensitive Staphylococcus aureus; MRSA, methicillin‐resistant Staphylococcus aureus. *Clustered by patient.

Age, per 10 years increase in age 0.80 0.73‐0.87 <0.001
Year of discharge
2012 0.47 0.34‐0.67 <0.001
2013 1.10 0.84‐1.43 0.493
2014 Ref
Race/ethnicity
White non‐Hispanic Ref
Black non‐Hispanic 0.89 0.64‐1.22 0.454
Hispanic 1.01 0.70‐1.46 0.952
Asian 0.85 0.40‐1.83 0.679
Other or unknown 1.29 0.73‐2.26 0.378
Insurance
Medicare Ref
Medicaid 1.99 1.29‐3.05 0.002
Dual 1.06 0.72‐1.57 0.765
Private 1.13 0.70‐1.82 0.620
Indigent/self‐pay 1.66 0.95‐2.88 0.073
Other 0.96 0.47‐1.96 0.908
Discharge disposition
Home with self‐care Ref
Home with home health 4.48 3.10‐6.48 <0.001
Hospicehome or inpatient 2.11 0.98‐4.55 0.057
Postacute‐care facility or LTAC 10.37 6.92‐15.56 <0.001
Expired 5.38 2.27‐12.75 <0.001
Other 4.04 2.64‐6.18 <0.001
No. of admission medications 1.00 0.99‐1.02 0.775
Primary diagnosis by ICD‐9 code
Sepsis, unspecified 1.11 0.78‐1.58 0.575
MSSA septicemia 2.44 0.68‐8.67 0.074
MRSA septicemia 8.83 1.72‐45.36 0.009
Alcoholic cirrhosis of the liver 1.25 0.43‐3.65 0.687
Palliative care consult 4.63 2.86‐7.49 <0.001
ICU stay 6.66 5.22‐8.50 <0.001
Surgical procedure 5.04 3.90‐6.52 <0.001

Sensitivity analyses using LOS >14 and >30 days yielded similar results to LOS >21 days (see Supporting Appendix Table 1 in the online version of this article).

DISCUSSION

We found that a small proportion of medicine patients with prolonged hospitalizations contributed substantially to both total inpatient days and average inpatient LOS. Such disproportionate healthcare utilization is concerning in light of the Institute of Medicine's charge for health systems to deliver timely, efficient, and equitable care.[11]

Few studies in the United States have analyzed patient characteristics that predict prolonged LOS, and to our knowledge, none have evaluated prolonged LOS specifically in general medicine patients.[12, 13, 14] Among selected surgical populations, prolonged hospitalizations are most often related to placement difficulties, operational delays, and payer‐related issues, rather than severity of illness, baseline comorbidities, or in‐hospital complications.[12, 13] In our study, we found that patients with prolonged LOS were more likely to require a palliative care consult, ICU stay, or surgery, all proxies for disease severity. Patients with prolonged LOS were also more likely to undergo surgery >24 hours after admission than those without prolonged LOS, suggesting that the former were either too unstable to proceed directly to surgery or developed complications later during their hospitalization. Even after controlling for palliative care consults, ICU stays, and surgeries, placement at a postacute‐care facility was strongly associated with prolonged LOS. Patients with prolonged LOS were also more likely to have Medicaid compared to other insurance types.

Our findings have several potential implications for efforts aimed at decreasing the number of and length of prolonged hospitalizations. Although demographic and clinical factors such as Medicaid insurance, ICU stays, and surgeries are generally not modifiable, they could, particularly in combination, be used to trigger earlier and more intensive case management involvement. A streamlined insurance approval process for Medicaid pending inpatients could be beneficial, given the recent expansion of Medicaid eligibility under the ACA. Hospital partnerships with postacute‐care facilities could also relieve bottlenecks in placement.[8] Chart review of the patients with MRSA septicemia and prolonged LOS indicated that development of an intensive outpatient parenteral antimicrobial therapy pathway with substance abuse counseling could provide an alternative to extended inpatient treatment for intravenous drug users with complicated infections.[15]

This study has several limitations. First, given the lack of consensus in the literature regarding the definition of a prolonged hospitalization, it is difficult to directly compare our results with existing studies.[8, 12, 13, 14] However, we believe LOS >21 days to be a meaningful cutoff for our cohort. Most demographic and clinical variables that were predictive at >21 days were also predictive at >14 and >30 days, which reassured us that the relationship between variables and prolonged LOS was stable at different thresholds. Second, our database did not allow us to fully adjust for baseline comorbidities or categorize the reasons for discharge delays. Finally, this was a single‐center program evaluation. Although this limits generalization to other institutions, we believe our approach may serve as a guide for others interested in reducing prolonged hospitalizations.

In summary, prolonged hospitalizations represent a potentially high‐yield target for LOS reduction efforts. Prolonged hospitalizations among medicine patients at our institution particularly affected Medicaid enrollees with complex hospital stays who were not discharged home. Further studies are needed to determine the specific reasons for unnecessary hospital days in this population.

Acknowledgements

The authors thank Essey Yirdaw for her contributions to the building and management of the database that informed this work.

Disclosure: M.E.A. conceived of the study concept and design and drafted the manuscript. J.J.G. assisted with the study design and made critical revisions to the final manuscript. D.A., R.P., and R.C. assisted with the study design and made critical revisions to the manuscript. C.D.J. assisted with the study design, performed data analyses, and made critical revisions to the manuscript. RC has disclosed that her time is funded by a National Institutes of Health grant unrelated to this study. A modified abstract was presented in poster format at the Society of Hospital Medicine Research, Innovations, and Vignettes Competition 2015 Annual Meeting, held March 29 April 1, 2015, in National Harbor, Maryland. The authors have no conflicts of interest to disclose.

References
  1. Kim CS, Hart AL, Paretti RF, et al. Excess hospitalization days in an academic medical center: perceptions of hospitalists and discharge planners. Am J Manag Care. 2011;17(2):e34e42.
  2. Carey MR, Sheth H, Braithwaite RS. A prospective study of reasons for prolonged hospitalizations on a general medicine teaching service. J Gen Intern Med. 2005;20(2):108115.
  3. DesRoches CM, Charles D, Furukawa MF, et al. Adoption of electronic health records grows rapidly, but fewer than half of U.S. hospitals had at least a basic system in 2012. Health Aff (Millwood). 2013;32(8):14781485.
  4. Sheehy AM, Caponi B, Gangireddy S, et al. Observation and inpatient status: clinical impact of the 2‐midnight rule. J Hosp Med. 2014;9(4):203209.
  5. DeLeire T, Joynt K, McDonald R. Impact of insurance expansion on hospital uncompensated care costs in 2014. Department of Health and Human Services Office of the Assistant Secretary for Planning and Evaluation. Available at: http://aspe.hhs.gov/health/reports/2014/uncompensatedcare/ib_uncompensatedcare.pdf. Accessed March 28, 2015.
  6. Resar R, Nolan K, Kaczynski D, Jensen K. Using real‐time demand capacity management to improve hospital‐wide patient flow. Jt Comm J Qual Patient Saf. 2011;37(5):217227.
  7. Chen LM, Freitag MH, Franco M, Sullivan CD, Dickson C, Brancati FL. Natural history of late discharges from a general medical ward. J Hosp Med. 2009;4(4):226233.
  8. Lagoe R, Pernisi L, Luziani M, Littau S. Addressing hospital length of stay outlier patients: a community‐wide approach. Adv Biosci Biotechol. 2014;5:188196.
  9. Milstein A, Gilbertson E. American medical home runs. Health Aff (Millwood). 2009;28(5):13171326.
  10. Gawande A. The hot spotters: can we lower medical costs by giving the neediest patients better care? New Yorker. January 2011:4051.
  11. Institute of Medicine. Crossing the Quality Chasm. Washington, DC: National Academies Press; 2001.
  12. Hwabejire JO, Kaafarani HM, Imam AM, et al. Excessively long hospital stays after trauma are not related to the severity of illness: let's aim to the right target! JAMA Surg. 2013;148(1):956961.
  13. Krell RW, Girotti ME, Dimick JB. Extended length of stay after surgery: complications, inefficient practice, or sick patients? JAMA Surg. 2014;149(8):815820.
  14. Foer D, Ornstein K, Soriano TA, Kathuria N, Dunn A. Nonmedical factors associated with prolonged hospital length of stay in an urban homebound population. J Hosp Med. 2012;7(2):7378.
  15. Ho J, Archuleta S, Sulaiman Z, Fisher D. Safe and successful treatment of intravenous drug users with a peripherally inserted central catheter in an outpatient parenteral antibiotic treatment service. J Antimicrob Chemother. 2010;65(12):26412644.
References
  1. Kim CS, Hart AL, Paretti RF, et al. Excess hospitalization days in an academic medical center: perceptions of hospitalists and discharge planners. Am J Manag Care. 2011;17(2):e34e42.
  2. Carey MR, Sheth H, Braithwaite RS. A prospective study of reasons for prolonged hospitalizations on a general medicine teaching service. J Gen Intern Med. 2005;20(2):108115.
  3. DesRoches CM, Charles D, Furukawa MF, et al. Adoption of electronic health records grows rapidly, but fewer than half of U.S. hospitals had at least a basic system in 2012. Health Aff (Millwood). 2013;32(8):14781485.
  4. Sheehy AM, Caponi B, Gangireddy S, et al. Observation and inpatient status: clinical impact of the 2‐midnight rule. J Hosp Med. 2014;9(4):203209.
  5. DeLeire T, Joynt K, McDonald R. Impact of insurance expansion on hospital uncompensated care costs in 2014. Department of Health and Human Services Office of the Assistant Secretary for Planning and Evaluation. Available at: http://aspe.hhs.gov/health/reports/2014/uncompensatedcare/ib_uncompensatedcare.pdf. Accessed March 28, 2015.
  6. Resar R, Nolan K, Kaczynski D, Jensen K. Using real‐time demand capacity management to improve hospital‐wide patient flow. Jt Comm J Qual Patient Saf. 2011;37(5):217227.
  7. Chen LM, Freitag MH, Franco M, Sullivan CD, Dickson C, Brancati FL. Natural history of late discharges from a general medical ward. J Hosp Med. 2009;4(4):226233.
  8. Lagoe R, Pernisi L, Luziani M, Littau S. Addressing hospital length of stay outlier patients: a community‐wide approach. Adv Biosci Biotechol. 2014;5:188196.
  9. Milstein A, Gilbertson E. American medical home runs. Health Aff (Millwood). 2009;28(5):13171326.
  10. Gawande A. The hot spotters: can we lower medical costs by giving the neediest patients better care? New Yorker. January 2011:4051.
  11. Institute of Medicine. Crossing the Quality Chasm. Washington, DC: National Academies Press; 2001.
  12. Hwabejire JO, Kaafarani HM, Imam AM, et al. Excessively long hospital stays after trauma are not related to the severity of illness: let's aim to the right target! JAMA Surg. 2013;148(1):956961.
  13. Krell RW, Girotti ME, Dimick JB. Extended length of stay after surgery: complications, inefficient practice, or sick patients? JAMA Surg. 2014;149(8):815820.
  14. Foer D, Ornstein K, Soriano TA, Kathuria N, Dunn A. Nonmedical factors associated with prolonged hospital length of stay in an urban homebound population. J Hosp Med. 2012;7(2):7378.
  15. Ho J, Archuleta S, Sulaiman Z, Fisher D. Safe and successful treatment of intravenous drug users with a peripherally inserted central catheter in an outpatient parenteral antibiotic treatment service. J Antimicrob Chemother. 2010;65(12):26412644.
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Understanding predictors of prolonged hospitalizations among general medicine patients: A guide and preliminary analysis
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Hospital Medicine Management Dictums

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Hospital medicine viewed through practice management dictums

In the spring of 1998 at the Society of Hospital Medicine's (SHM) (then known as the National Association of Inpatient Physicians) first annual meeting, Dr. John Eisenberg asked, If the hospitalist model of practice were a drug, do we have enough evidence about its risks and benefits to support its use? His question is only one of many often‐repeated dictums and phrases regarding how the hospitalist model of practice is organized and performs. These can serve as useful lenses to assess the past and future of the field.

Data and opinions used to answer Dr. Eisenberg's question continue to evolve. Many studies and opinions of its effects on costs and quality have appeared in the peer‐reviewed literature, including the Journal of Hospital Medicine, which has become a principal home for studies of the hospitalist model of care. In 1998, hospital medicine's impact on outcomes and costs was only beginning, and descriptions of the hospitalist's role in implementation of new programs, such as team‐based rounding models, geographic assignment of hospitalists, or the costs of interruptions, were not even on our radar. Effective management of these and other operational concerns will help ensure we are able to answer Dr. Eisenberg's question with an increasingly confident yes.

Early in the history of hospital medicine, it became common to speak of the voltage drop of information loss as a patient's care transitions to and from hospitalists and other caregivers. This term remains in common use today and encourages a focus on handoff communication. As of April 2015, the Journal of Hospital Medicine has published 15 articles that mention handoffs in the title, and many more that address the topic more peripherally.[1] Collectively, these provide thoughtful strategies to mitigate a voltage drop and its risks,[2] even though it persists and more work is needed to overcome it.

Referring to work as a hospitalist, many have said that this is a young doctor's game; one cannot do it for a whole career. The field is young enough that one cannot convincingly prove or disprove this idea, and evidence can be found on either side. Hospitalist burnout is distressingly common, though potentially similar to many other physician specialties.[3, 4, 5] Through both peer‐reviewed literature and more informal channels, primarily SHM activities, there is a substantial and growing set of data and opinions regarding factors related to burnout and potential mitigation strategies.

Donald Redelmeier observed that a hospitalist's time is to a large degree governed by a pager, in contrast to an office‐based physician whose time is governed by a clock.[6] Frequent interruptions delivered by a pager, many of which are of low importance and not urgent, are a significant issue for hospitalists, and to some extent all healthcare providers, and one begging for solutions.[7] Technology that replaces pagers will be helpful and will need to be paired with new methods around what is communicated, how urgently, and by what method.

Perhaps the most common dictum used by those who think about sharing best practices across our field is: If you have seen one hospitalist practice, you have seen one hospitalist practice. This has been invoked countless times as shorthand for the myriad ways hospitalist practices are organized, differing significantly in scheduling, workloads, compensation, leadership, cost structure, and other operational details. Here, the SHM serves as a valuable forum for exchange of ideas and information about the relative merits of different operational structures, and in 2014 published expert opinion regarding valuable characteristics of hospital medicine groups associated with success.[8]

In the 1990s, the principal mission of a hospitalist group was to replace primary care physicians who were leaving hospital practice and to increase efficiency of care. Many activities have since been added to this still‐important original mission, including improving performance on patient safety, quality, and satisfaction, and ensuring good hospital performance during the transition to dramatically different forms of reimbursement for services. Moreover, hospitals are increasingly organized into networks, most of which are now seeking to reduce variation in hospitalist organizational models and performance across all of their hospitals.[9]

This final dictum is a foundational one for our field, and will help us solve the challenges posed by the others: A hospitalist's job is to provide care for the sick person occupying a room in the hospital, and to care for and improve the performance of the hospital itself. Laurence Wellikson, Chief Executive Officer of the SHM, may have said this first. By embracing both of these goals, hospitalists have the opportunity to achieve much on behalf of individual patients and the healthcare system as a whole.

New dictums and sayings are sure to arise, and there is ample room for optimism that they will increasingly highlight the successes and vital role of hospital medicine.

Disclosure

Nothing to report.

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References
  1. Journal of Hospital Medicine website. Available at: http://onlinelibrary.wiley.com/journal/10.1002/%28ISSN%291553‐5606. Accessed April 8, 2015.
  2. Jones CD, Glasheen JJ. Handoffs: a story in evolution. J Hosp Med. 2015;10(3):202203.
  3. Roberts DL, Shanafelt TD, Dyrbye LN, West CP. A national comparison of burnout and work‐life balance among internal medicine hospitalists and outpatient general internists. J Hosp Med. 2014;9(3):176181.
  4. Hinami K, Whelan CT, Wolosin RJ, Miller JA, Wetterneck TB. Worklife and satisfaction of hospitalists: toward flourishing careers. J Gen Intern Med. 2012;27(1):2836.
  5. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB; Society of Hospital Medicine Career Satisfaction Task Force. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7(5):402410.
  6. Redelmeier DA. A Canadian perspective on the American hospitalist movement. Arch Intern Med. 1999;159(15):16651668.
  7. Tipping MD, Forth VE, Magill DB, Englert K, Williams MV. Systematic review of time studies evaluating physicians in the hospital setting. J Hosp Med. 2010;5(6):353359.
  8. Cawley P, Deitelzweig S, Flores L, et al. The key principles and characteristics of an effective hospital medicine group: an assessment guide for hospitals and hospitalists. J Hosp Med. 2014;9(2):123128.
  9. Nelson J. Multi‐site hospital medicine group leaders face similar challenges. The Hospitalist. November 1, 2013. Available at: http://www.the‐hospitalist.org/article/multi‐site‐hospital‐medicine‐group‐leaders‐face‐similar‐challenges. Accessed April 8, 2015.
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In the spring of 1998 at the Society of Hospital Medicine's (SHM) (then known as the National Association of Inpatient Physicians) first annual meeting, Dr. John Eisenberg asked, If the hospitalist model of practice were a drug, do we have enough evidence about its risks and benefits to support its use? His question is only one of many often‐repeated dictums and phrases regarding how the hospitalist model of practice is organized and performs. These can serve as useful lenses to assess the past and future of the field.

Data and opinions used to answer Dr. Eisenberg's question continue to evolve. Many studies and opinions of its effects on costs and quality have appeared in the peer‐reviewed literature, including the Journal of Hospital Medicine, which has become a principal home for studies of the hospitalist model of care. In 1998, hospital medicine's impact on outcomes and costs was only beginning, and descriptions of the hospitalist's role in implementation of new programs, such as team‐based rounding models, geographic assignment of hospitalists, or the costs of interruptions, were not even on our radar. Effective management of these and other operational concerns will help ensure we are able to answer Dr. Eisenberg's question with an increasingly confident yes.

Early in the history of hospital medicine, it became common to speak of the voltage drop of information loss as a patient's care transitions to and from hospitalists and other caregivers. This term remains in common use today and encourages a focus on handoff communication. As of April 2015, the Journal of Hospital Medicine has published 15 articles that mention handoffs in the title, and many more that address the topic more peripherally.[1] Collectively, these provide thoughtful strategies to mitigate a voltage drop and its risks,[2] even though it persists and more work is needed to overcome it.

Referring to work as a hospitalist, many have said that this is a young doctor's game; one cannot do it for a whole career. The field is young enough that one cannot convincingly prove or disprove this idea, and evidence can be found on either side. Hospitalist burnout is distressingly common, though potentially similar to many other physician specialties.[3, 4, 5] Through both peer‐reviewed literature and more informal channels, primarily SHM activities, there is a substantial and growing set of data and opinions regarding factors related to burnout and potential mitigation strategies.

Donald Redelmeier observed that a hospitalist's time is to a large degree governed by a pager, in contrast to an office‐based physician whose time is governed by a clock.[6] Frequent interruptions delivered by a pager, many of which are of low importance and not urgent, are a significant issue for hospitalists, and to some extent all healthcare providers, and one begging for solutions.[7] Technology that replaces pagers will be helpful and will need to be paired with new methods around what is communicated, how urgently, and by what method.

Perhaps the most common dictum used by those who think about sharing best practices across our field is: If you have seen one hospitalist practice, you have seen one hospitalist practice. This has been invoked countless times as shorthand for the myriad ways hospitalist practices are organized, differing significantly in scheduling, workloads, compensation, leadership, cost structure, and other operational details. Here, the SHM serves as a valuable forum for exchange of ideas and information about the relative merits of different operational structures, and in 2014 published expert opinion regarding valuable characteristics of hospital medicine groups associated with success.[8]

In the 1990s, the principal mission of a hospitalist group was to replace primary care physicians who were leaving hospital practice and to increase efficiency of care. Many activities have since been added to this still‐important original mission, including improving performance on patient safety, quality, and satisfaction, and ensuring good hospital performance during the transition to dramatically different forms of reimbursement for services. Moreover, hospitals are increasingly organized into networks, most of which are now seeking to reduce variation in hospitalist organizational models and performance across all of their hospitals.[9]

This final dictum is a foundational one for our field, and will help us solve the challenges posed by the others: A hospitalist's job is to provide care for the sick person occupying a room in the hospital, and to care for and improve the performance of the hospital itself. Laurence Wellikson, Chief Executive Officer of the SHM, may have said this first. By embracing both of these goals, hospitalists have the opportunity to achieve much on behalf of individual patients and the healthcare system as a whole.

New dictums and sayings are sure to arise, and there is ample room for optimism that they will increasingly highlight the successes and vital role of hospital medicine.

Disclosure

Nothing to report.

In the spring of 1998 at the Society of Hospital Medicine's (SHM) (then known as the National Association of Inpatient Physicians) first annual meeting, Dr. John Eisenberg asked, If the hospitalist model of practice were a drug, do we have enough evidence about its risks and benefits to support its use? His question is only one of many often‐repeated dictums and phrases regarding how the hospitalist model of practice is organized and performs. These can serve as useful lenses to assess the past and future of the field.

Data and opinions used to answer Dr. Eisenberg's question continue to evolve. Many studies and opinions of its effects on costs and quality have appeared in the peer‐reviewed literature, including the Journal of Hospital Medicine, which has become a principal home for studies of the hospitalist model of care. In 1998, hospital medicine's impact on outcomes and costs was only beginning, and descriptions of the hospitalist's role in implementation of new programs, such as team‐based rounding models, geographic assignment of hospitalists, or the costs of interruptions, were not even on our radar. Effective management of these and other operational concerns will help ensure we are able to answer Dr. Eisenberg's question with an increasingly confident yes.

Early in the history of hospital medicine, it became common to speak of the voltage drop of information loss as a patient's care transitions to and from hospitalists and other caregivers. This term remains in common use today and encourages a focus on handoff communication. As of April 2015, the Journal of Hospital Medicine has published 15 articles that mention handoffs in the title, and many more that address the topic more peripherally.[1] Collectively, these provide thoughtful strategies to mitigate a voltage drop and its risks,[2] even though it persists and more work is needed to overcome it.

Referring to work as a hospitalist, many have said that this is a young doctor's game; one cannot do it for a whole career. The field is young enough that one cannot convincingly prove or disprove this idea, and evidence can be found on either side. Hospitalist burnout is distressingly common, though potentially similar to many other physician specialties.[3, 4, 5] Through both peer‐reviewed literature and more informal channels, primarily SHM activities, there is a substantial and growing set of data and opinions regarding factors related to burnout and potential mitigation strategies.

Donald Redelmeier observed that a hospitalist's time is to a large degree governed by a pager, in contrast to an office‐based physician whose time is governed by a clock.[6] Frequent interruptions delivered by a pager, many of which are of low importance and not urgent, are a significant issue for hospitalists, and to some extent all healthcare providers, and one begging for solutions.[7] Technology that replaces pagers will be helpful and will need to be paired with new methods around what is communicated, how urgently, and by what method.

Perhaps the most common dictum used by those who think about sharing best practices across our field is: If you have seen one hospitalist practice, you have seen one hospitalist practice. This has been invoked countless times as shorthand for the myriad ways hospitalist practices are organized, differing significantly in scheduling, workloads, compensation, leadership, cost structure, and other operational details. Here, the SHM serves as a valuable forum for exchange of ideas and information about the relative merits of different operational structures, and in 2014 published expert opinion regarding valuable characteristics of hospital medicine groups associated with success.[8]

In the 1990s, the principal mission of a hospitalist group was to replace primary care physicians who were leaving hospital practice and to increase efficiency of care. Many activities have since been added to this still‐important original mission, including improving performance on patient safety, quality, and satisfaction, and ensuring good hospital performance during the transition to dramatically different forms of reimbursement for services. Moreover, hospitals are increasingly organized into networks, most of which are now seeking to reduce variation in hospitalist organizational models and performance across all of their hospitals.[9]

This final dictum is a foundational one for our field, and will help us solve the challenges posed by the others: A hospitalist's job is to provide care for the sick person occupying a room in the hospital, and to care for and improve the performance of the hospital itself. Laurence Wellikson, Chief Executive Officer of the SHM, may have said this first. By embracing both of these goals, hospitalists have the opportunity to achieve much on behalf of individual patients and the healthcare system as a whole.

New dictums and sayings are sure to arise, and there is ample room for optimism that they will increasingly highlight the successes and vital role of hospital medicine.

Disclosure

Nothing to report.

References
  1. Journal of Hospital Medicine website. Available at: http://onlinelibrary.wiley.com/journal/10.1002/%28ISSN%291553‐5606. Accessed April 8, 2015.
  2. Jones CD, Glasheen JJ. Handoffs: a story in evolution. J Hosp Med. 2015;10(3):202203.
  3. Roberts DL, Shanafelt TD, Dyrbye LN, West CP. A national comparison of burnout and work‐life balance among internal medicine hospitalists and outpatient general internists. J Hosp Med. 2014;9(3):176181.
  4. Hinami K, Whelan CT, Wolosin RJ, Miller JA, Wetterneck TB. Worklife and satisfaction of hospitalists: toward flourishing careers. J Gen Intern Med. 2012;27(1):2836.
  5. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB; Society of Hospital Medicine Career Satisfaction Task Force. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7(5):402410.
  6. Redelmeier DA. A Canadian perspective on the American hospitalist movement. Arch Intern Med. 1999;159(15):16651668.
  7. Tipping MD, Forth VE, Magill DB, Englert K, Williams MV. Systematic review of time studies evaluating physicians in the hospital setting. J Hosp Med. 2010;5(6):353359.
  8. Cawley P, Deitelzweig S, Flores L, et al. The key principles and characteristics of an effective hospital medicine group: an assessment guide for hospitals and hospitalists. J Hosp Med. 2014;9(2):123128.
  9. Nelson J. Multi‐site hospital medicine group leaders face similar challenges. The Hospitalist. November 1, 2013. Available at: http://www.the‐hospitalist.org/article/multi‐site‐hospital‐medicine‐group‐leaders‐face‐similar‐challenges. Accessed April 8, 2015.
References
  1. Journal of Hospital Medicine website. Available at: http://onlinelibrary.wiley.com/journal/10.1002/%28ISSN%291553‐5606. Accessed April 8, 2015.
  2. Jones CD, Glasheen JJ. Handoffs: a story in evolution. J Hosp Med. 2015;10(3):202203.
  3. Roberts DL, Shanafelt TD, Dyrbye LN, West CP. A national comparison of burnout and work‐life balance among internal medicine hospitalists and outpatient general internists. J Hosp Med. 2014;9(3):176181.
  4. Hinami K, Whelan CT, Wolosin RJ, Miller JA, Wetterneck TB. Worklife and satisfaction of hospitalists: toward flourishing careers. J Gen Intern Med. 2012;27(1):2836.
  5. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB; Society of Hospital Medicine Career Satisfaction Task Force. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7(5):402410.
  6. Redelmeier DA. A Canadian perspective on the American hospitalist movement. Arch Intern Med. 1999;159(15):16651668.
  7. Tipping MD, Forth VE, Magill DB, Englert K, Williams MV. Systematic review of time studies evaluating physicians in the hospital setting. J Hosp Med. 2010;5(6):353359.
  8. Cawley P, Deitelzweig S, Flores L, et al. The key principles and characteristics of an effective hospital medicine group: an assessment guide for hospitals and hospitalists. J Hosp Med. 2014;9(2):123128.
  9. Nelson J. Multi‐site hospital medicine group leaders face similar challenges. The Hospitalist. November 1, 2013. Available at: http://www.the‐hospitalist.org/article/multi‐site‐hospital‐medicine‐group‐leaders‐face‐similar‐challenges. Accessed April 8, 2015.
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Journal of Hospital Medicine - 10(9)
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Hospital medicine viewed through practice management dictums
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Hospital medicine viewed through practice management dictums
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Address for correspondence and reprint requests: John R. Nelson, MD, Overlake Medical Center, 1034 NE 116th Ave., Bellevue, WA 98005; Telephone: 425‐467‐3316; Fax: 425‐467‐3310; E‐mail: [email protected]
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Priorities and Gender Pay Gap

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A matter of priorities? Exploring the persistent gender pay gap in hospital medicine

Hospitalists are a growing workforce numbering over 40,000 physicians, one‐third of whom are women.[1] Flexibility of work schedules and control over personal time have been the traditional selling points of the specialty.[2] Multiple studies of physician work life reveal growing physician dissatisfaction and a high prevalence of burnout.[3] To mitigate burnout risk, leaders in hospital medicine recognize the importance of creating a sustainable profession that offers both job and career satisfaction as well as work‐life balance and, importantly, fairness within the work environment.[4] Although success in some of these endeavors has been realized sporadically, sustaining work‐life balance and fairness in the specialty remains a work in progress, whereas evidence of high job attrition and pay inequities remain.[5, 6]

Pay inequity for women relative to men continues to be pervasive in medicine, including among early‐career physicians, researchers, and various specialists.[6, 7, 8, 9, 10, 11, 12, 13] The earnings gap seems to persist for physicians, even as federal efforts such as the Fair Pay Act of 2013 and the Paycheck Fairness Act of 2014 aim to end wage discrimination.[11, 14] Differences in specialty, part‐time status, and practice type do not mitigate the disparity.[8, 10, 15] Additional explanations have been proposed to explain the variability, including gender differences in negotiating skills, lack of opportunities to join networks of influence within organizations, and implicit or explicit bias and discrimination.[12, 16, 17, 18, 19, 20]

The earnings gap is also a consequence of what is commonly called the glass ceiling.[18, 19] Most agree that obstacles to fair advancement of women include absence of collaborative environments and role models who have successfully achieved work‐life balance.[17, 20, 21, 22] Somewhat surprisingly, women leaders in medicine seem to suffer greater income disparity than nonleaders; this income gap is prevalent among leaders in other elite professions as well.[7, 23] It is unknown whether women physicians' emphasis on work‐life balance, seen repeatedly in surveys, explains any of the pay disparity.[24] Little research to date has examined whether work‐life priorities of women in hospital medicine differ from men.

In this study, we sought to examine differences in job priorities between men and women hospitalists. In particular, we examine the relative prioritization of substantial pay to job satisfaction. We also examined gender differences in work patterns and earnings to explore potential sources of the persistent gender earnings gap.

METHODS

We analyzed data from the 20092010 Hospital Medicine Physician Worklife Survey, the design of which is detailed elsewhere.[4] Briefly, a 118‐item survey was administered by mail to a stratified sample of hospitalists from the Society of Hospital Medicine database and 3 large multisite hospitalist groups. A single survey item asked respondents to identify up to 4 out of 12 most important domains to their satisfaction with a hospitalist job. The domains were distilled from focus groups of nationally representative hospitalists as described previously,[4] and the survey item allowed up to one‐third of these domains to be identified as respondents' personal priorities. The list included: optimal variety of tasks, optimal workload, substantial pay, collegiality with other physicians, recognition by leaders, rewarding relationships with patients, satisfaction with nurses, optimal autonomy, control over personal time, fairness within organization, ample availability of resources to do job, and organizational climate of trust and belonging. We tabulated and ranked the frequency with which respondents selected each satisfaction domain by gender. Due to the nonstandard format of the survey item, we a priori decided to analyze only responses that were completed as instructed.

We also used demographic data including detailed work characteristics, clinical and nonclinical workload, total pretax earnings in 2009 as a hospitalist, and self‐identification as leader of their hospital medicine group. Respondent characteristics were tabulated and gender differences were tested using the t test, rank sum test, and the Fischer exact test as appropriate. We also listed the number of nonrespondents for each item. In estimating gender differences in earnings, we opted to use multiple‐imputation techniques to more conservatively account for greater variance inherent in the presence of missing data. Consistent with existing guidelines,[25] we demonstrated that item responses were not missing monotonically by visually inspecting patterns of nonresponse. We further demonstrated that data were missing at random by showing that response patterns of completed survey items did not predict whether or not a given variable response was missing using logistic regression models. We found no significant differences between respondents with complete and missing data. We verified that appropriate regression models for each variable on every other variable converged. We used Stata 13.1 (StataCorp, College Station, TX) to perform multiple imputations using chain equations (mi impute chain) to create 10 imputed tables for 7 normally distributed continuous variables using the ordinary least squares method, 3 non‐normally distributed variables using the predictive mean matching method, 2 nonordinal categorical variables using the multinomial logit method, and 1 binary variable using the logit method.[26, 27] Gender, pediatric specialty status, region of practice, and whether or not respondents prioritized substantial pay for job satisfaction were used as regular variables without missing data points.

Differences in earnings were assessed using a multivariate ordinary linear regression model applied to the imputed datasets fitted by forward selection of explanatory variables using P < 0.20 in bivariate analysis for inclusion and manual backward elimination of all statistically nonsignificant variables. We tested the significance of the women leader interaction term in the final parsimonious model. We used the usual significance threshold of P < 0.05 for inferences. Our analysis of publicly available anonymous data was exempt from IRB review.

RESULTS

Of the 816 survey respondents (response rate 25.6%), 40 either omitted the item soliciting work priorities or completed it incorrectly. Data from the remaining 776 respondents were used for the present analysis. Respondent characteristics are tabulated in Table 1. The characteristics of hospitalists by age, gender, specialty, practice model, and practice region were representative of US hospitalists from other surveys.[28]

Differences in Characteristics and Work Patterns of Women Compared to Men Hospitalists
 WomenMenP ValueNo. of Missing Responses
  • NOTE: Abbreviations: DP, domestic partnership; FTE, full‐time equivalent; IQR, interquartile range; SD, standard deviation.

No.263513 0
Role, n (%)  <0.010
Frontline hospitalist201 (76)337 (66)  
Hospitalist leader53 (24)176 (34)  
Age, y, mean (SD)42 (8)45 (9)<0.0167
Years in current job, mean (SD)5 (4)6 (5)0.0714
Specialty, n (%)  <0.010
Internal medicine160 (61)369 (72)  
Pediatrics56 (21)57 (11)  
Other39 (15)47 (9)  
Family medicine8 (3)40 (8)  
Practice model, n (%)  0.0219
Hospital employed110 (43)227 (46)  
Multispecialty group44 (17)68 (14)  
University/medical school47 (18)58 (12)  
Multistate group27 (11)73 (15)  
Local hospitalist group22 (8)65 (13)  
Other7 (3)9 (2)  
Practice region, n (%)  0.140
Southeast56 (21)151 (29)  
Midwest58 (22)106 (21)  
Northeast54 (21)96 (19)  
Southwest44 (17)83 (16)  
West51 (19)77 (15)  
Full‐time equivalents, n (%)  <0.0142
<100%46 (18)60 (12)  
100%202 (81)402 (83)  
>100%2 (1)22 (5)  
Days per month doing clinical work if FTE 100%, median (IQR)15 (1418)16 (1420)0.1211
Hours per day doing clinical work, median (IQR)11 (912)11 (912)0.6730
Consecutive days doing clinical work, median (IQR)7 (57)7 (57)0.9417
Percentage of work at night, median (IQR)15 (530)15 (525)0.4516
Percentage of night work in hospital if working nights, median (IQR)100 (5100)100 (10100)0.128
Hours per month doing nonclinical work, median (IQR)12 (540)15 (540)0.7726
Estimated daily billable encounters, mean (IQR)14 (1116)15 (1218)0.0154
Total earnings in fiscal year 2009, median US$1,000 (IQR)185 (150210)202 (180240)<0.0156
Marriage/domestic partnership status, n (%)  0.1543
Married/currently in DP197 (80)421 (86)  
Never married/never in DP26 (11)42 (9)  
Divorced or separated18 (7)20 (4)  
Other4 (2)5 (1)  
Dependent children under 7 years old living in home, n (%)  0.2242
0136 (55)265 (54)  
147 (19)92 (19)  
252 (21)87 (18)  
312 (5)43 (9)  

Several gender differences were seen in the characteristics of hospitalists and their work (Table 1). Women compared to men hospitalists were less likely to be leaders, more likely to be pediatricians, work in university settings, and practice in Western states. Women compared to men, on average, were younger by 3 years, worked fewer full‐time equivalents (FTEs), worked a greater percentage of nights, and reported fewer billable encounters per shift. They were also more likely to be divorced or separated.

Job satisfaction priorities differed for women and men hospitalists. Table 2 lists job satisfaction domains in descending order of the frequency prioritized by men. The largest proportion of women and men prioritized optimal workload. However, although substantial pay was prioritized next most frequently by men, more women prioritized collegiality and control over personal time than substantial pay.

Percentage of Women and Men Who Indicated That a Domain Was One of Up to Four Most Important Factors to Her/His Job Satisfaction
 Women, %RankMen, %Rank
Optimal workload591591
Substantial pay414502
Control over personal time443413
Collegiality with physicians472384
Rewarding relationships with patients355345
Organizational climate of trust and belonging277336
Ample availability of resources to do job249277
Optimal autonomy268248
Fairness within organization1510239
Optimal variety of tasks2962210
Recognition by leaders11121011
Satisfaction with nurses1211712

Key differences in individual characteristics, work patterns, and indicating substantial pay as a priority were associated with self‐reported total earnings in 2009 from respondents' work as a hospitalist. As shown in Table 3, the inclusion of detailed productivity measures such as FTE, days of monthly clinical work, and estimated number of daily billable encounters yielded a model that explained 33% of variance in earnings. After adjusting for significant covariates including pediatric specialty, practice model, geography, and amount and type of clinical work, the estimated underpayment of women compared to men was $14,581. Hospitalists who prioritized substantial pay earned $10,771 more than those who did not. The female x leader interaction term testing the hypothesis that gender disparity is greater among leaders than frontline hospitalists was not statistically significant ($16,720, P = 0.087) and excluded from the final model.

Ordinary Linear Regression Model Incorporating Multiple Imputation Estimates to Examine Adjusted Gender Differences in Hospitalists' Self‐Reported Earnings in 2009 US Dollars
 Differences in Salary, 2009 US$ (95% CI)P Value
  • NOTE: Abbreviations: CI, confidence interval; FTE, full‐time equivalent.

Women14,581 (23,074 to 6,089)<0.01
Leader21,997 (13,313 to 30,682)<0.01
Prioritized substantial pay10,771 (2,651 to 18,891)<0.01
Pediatric specialty31,126 (43,007 to 19,244)<0.01
Practice model  
Hospital employedREF 
Multispecialty group1,922 (13,891 to 10,047)0.75
University/medical school33,503 (46,336 to 20,671)<0.01
Multistate group6,505 (72,69 to 20,279)0.35
Local hospitalist group9,330 (4,352 to 23,012)0.18
Other17,364 (45,741 to 11,012)0.23
Practice region  
SoutheastREF 
Midwest1,225 (10,595 to 13,044)0.84
Northeast15,712 (28,182 to 3,242)0.01
Southwest722 (13,545 to 12,101)0.91
West5,251 (7,383 to 17,885)0.41
FTE1,021 (762 to 1,279)<0.01
Days per month doing clinical work1,209 (443 to 1,975)<0.01
Estimated daily billable encounters608 (20 to 1,196)0.04

DISCUSSION

In a national stratified sample of US hospitalists, we found gender differences in job satisfaction priorities and hospitalist work characteristics. We also confirmed the persistence of a substantial gender earnings disparity. Lower earnings among women compared to men hospitalists were present in our data after controlling for age, pediatric specialty, practice model, geography, type of clinical work, and productivity measures. The gender earnings disparity noted in 1999[6] persists, although it appears to have decreased, possibly indicating progress toward equity. We showed that women hospitalists' relative tendency not to prioritize pay explains a significant portion of the residual income gap.

Hoff examined hospitalist earnings in a large national survey of hospitalists in 1999. Our cohorts differed in age and experience (both lower in the Hoff study). An estimated $24,000 ($124,266 vs. $148,132) earnings gap between women and men was greater than our estimate of $14,581 following an interval of 10 years. Although survey items differed, both studies found that women were less interested in pay than men when considering a hospitalist job. Hoff also found that work setting and attitudes about pay and lifestyle were significantly related to earnings. We extended the previous analyses of gender differences in job satisfaction priorities, work, and demographic characteristics to explain the earnings gap and understand how it may be remedied.

When considering job satisfaction, we found that more men than women prioritized substantial pay and that prioritization of substantial pay was directly related to higher earnings. Therefore, fewer women prioritizing pay partly explains women's lower earnings. Reasons for why fewer women prioritize pay were not assessed in this study but may include factors like being part of 2‐income households and competing commitments.[29] Priorities may even be influenced by empirically observed gender differences in discussions of financial matters, governed by cultural norms. Such norms may implicitly sanction employers to offer women less pay than men for the same or similar work. Women may disadvantage themselves by negotiating less or less well than men for higher starting and promotion salaries. They may be perceived more negatively than men when they do negotiate pay, leading to unintended negative consequences such as loss of social networks, decreased likability, and even loss of job offers.[29, 30, 31, 32]

More women prioritized optimal variety of tasks (6th most prevalent among women and 10th among men). Women who highly rate optimal variety of tasks as a job satisfier may choose positions in which they teach, perform research, and participate in hospital committees and quality‐improvement work, but offer lower pay. Yet hours per month doing nonclinical work was not significantly different between men and women, nor associated with earnings differences in our earnings models. Understanding whether women self‐select into hospitalist jobs with like‐minded colleagues to achieve complementary fit or end up supplementing their skills with hospitalists with different priorities may inform strategies to reduce the gender income disparity.[5] Unlike disparities between various hospital medicine groups, systematic disparities within practices risk generating low levels of organizational fairness and burnout among employees.

Not surprisingly, productivity was positively associated with earnings but did not fully account for the gender earnings gap. Our data demonstrated that women, on average, were associated with work characteristics that expectedly generate less compensation. For example, women were younger, more often part time, academic, pediatric, less often leaders, and reported fewer billable encounters compared to men. These differences account for some of the earnings gap between men and women, but these factors were controlled for in the earnings model. In addition, our analysis may have underestimated the gap by not incorporating loss of fringe benefits from part‐time status and not comprehensively counting incentive pay associated with high productivity. Other work patterns more commonly associated with women suggest an imbalance in reimbursement. More women than men work nights that are often compensated at higher rates than daytime work, yet their average pay was less, suggesting that compensation for night work may need to be adjusted to reflect its unique burdens and responsibilities.[33]

Although the gender pay gap was not more extreme among leaders compared to frontline hospitalists in our data, the trend, nonetheless, underscores an important consideration. Whereas clinical work is paid for in mostly measurable ways, pay for leadership may be influenced by intangible factors such as reputation, negotiation, and confidence that may disadvantage women relative to men.[7, 19, 23, 34, 35, 36] Efforts to overcome implicit gender bias should be most effective when we consciously couple fair promotion of women to leadership with fair compensation commensurate with their male peers.[21]

Our data are vulnerable to nonresponse bias.[1, 4, 5] Post hoc analyses demonstrated that distributions of age, gender, practice model and region of our respondents were similar to other nationally representative cohorts of hospitalists. Consequently, we believe our data can make valid estimates about a nationally representative sample of hospitalists. However, we acknowledge several additional weaknesses of self‐reported data, including recall bias and accuracy of productivity figures, which were rounded to variable significant digits by respondents. Earnings analysis using this data was intended to be exploratory, but the findings echoed analyses using more authoritative data sources.[11] Still, we made inferences conservatively by adopting multiple imputation techniques for dealing with nonresponse surveys in adherence to established reporting guidelines.[25] We also note several limitations relevant to multiple imputations. The greater prevalence of missing data for survey items soliciting earnings and the number of billable encounters suggest they were not truly missing at random as assumed. However, we showed that missingness is unrelated to the variables under study, justifying use of the technique. The wider measures of variance derived from multiple imputations make us vulnerable to not detecting associations that may exist.

The gender earnings gap found in hospital medicine echoes the gap found in multiple medical specialties, including but not limited to pediatrics, academic medicine, gastroenterology, and plastic surgery.[7, 8, 9, 11, 12, 13, 37] Hospital medicine employment models and practice patterns have important structural differences compared to previously studied populations that could mitigate factors contributing to women physicians' lower earnings. However, despite well‐defined working hours, lack of control over the number of patient encounters per day and high prevalence of hospital‐employed practice models, the gender earnings gap persists. We showed that lower prioritization for pay may reflect the self‐selection of women into lower paying jobs. Unmeasured factors, including implicit bias and differences in negotiations, social networks and mentoring opportunities[38, 39] may also contribute to pay differences between men and women hospitalists. As hospital medicine tackles gender inequities and other disparities, strategies to assess and address fair physician compensation must be on the table.

Files
References
  1. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB; Society of Hospital Medicine Career Satisfaction Task F. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7(5):402410.
  2. Wachter RM, Goldman L. The emerging role of “hospitalists” in the American health care system. N Engl J Med. 1996;335(7):514517.
  3. Linzer M, Baier Manwell L, Mundt M, et al. Organizational climate, stress, and error in primary care: The MEMO study. In: Henriksen K, Battles JB, Marks ES, Lewin DI, eds. Advances in Patient Safety: From Research to Implementation. Vol. 1. Research Findings. Rockville, MD; Agency for Healthcare Research and Quality; 2005.
  4. Hinami K, Whelan CT, Wolosin RJ, Miller JA, Wetterneck TB. Worklife and satisfaction of hospitalists: toward flourishing careers. J Gen Intern Med. 2012;27(1):2836.
  5. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB. Person‐job fit: an exploratory cross‐sectional analysis of hospitalists. J Hosp Med. 2013;8(2):96101.
  6. Hoff TJ. Doing the same and earning less: male and female physicians in a new medical specialty. Inquiry. 2004;41(3):301315.
  7. Ash AS, Carr PL, Goldstein R, Friedman RH. Compensation and advancement of women in academic medicine: Is there equity? Ann Intern Med. 2004;141(3):205212.
  8. Baker LC. Differences in earnings between male and female physicians. N Engl J Med. 1996;334(15):960964.
  9. Jagsi R, Griffith KA, Stewart A, Sambuco D, DeCastro R, Ubel PA. Gender differences in the salaries of physician researchers. JAMA. 2012;307(22):24102417.
  10. McMurray JE, Linzer M, Konrad TR, Douglas J, Shugerman R, Nelson K. The work lives of women physicians results from the physician work life study. The SGIM Career Satisfaction Study Group. J Gen Intern Med. 2000;15(6):372380.
  11. Sasso AT, Richards MR, Chou CF, Gerber SE. The $16,819 pay gap for newly trained physicians: the unexplained trend of men earning more than women. Health Aff (Millwood). 2011;30(2):193201.
  12. Rotbart HA, McMillen D, Taussig H, Daniels SR. Assessing gender equity in a large academic department of pediatrics. Acad Med. 2012;87(1):98104.
  13. Burke CA, Sastri SV, Jacobsen G, Arlow FL, Karlstadt RG, Raymond P. Gender disparity in the practice of gastroenterology: the first 5 years of a career. Am J Gastroenterol. 2005;100(2):259264.
  14. H.R. 438, Fair Pay Act of 2013. 113th Congress (2013‐2014).
  15. Tracy EE, Wiler JL, Holschen JC, Patel SS, Ligda KO. Topics to ponder: part‐time practice and pay parity. Gend Med. 2010;7(4):350356.
  16. Carey EC, Weissman DE. Understanding and finding mentorship: a review for junior faculty. J Palliat Med. 2010;13(11):13731379.
  17. Fried LP, Francomano CA, MacDonald SM, et al. Career development for women in academic medicine: Multiple interventions in a department of medicine. JAMA. 1996;276(11):898905.
  18. Kaplan SH, Sullivan LM, Dukes KA, Phillips CF, Kelch RP, Schaller JG. Sex differences in academic advancement. Results of a national study of pediatricians. N Engl J Med. 1996;335(17):12821289.
  19. Tesch BJ, Wood HM, Helwig AL, Nattinger AB. Promotion of women physicians in academic medicine. Glass ceiling or sticky floor? JAMA. 1995;273(13):10221025.
  20. Levine RB, Lin F, Kern DE, Wright SM, Carrese J. Stories from early‐career women physicians who have left academic medicine: a qualitative study at a single institution. Acad Med. 2011;86(6):752758.
  21. Pololi LH, Civian JT, Brennan RT, Dottolo AL, Krupat E. Experiencing the culture of academic medicine: gender matters, a national study. J Gen Intern Med. 2013;28(2):201207.
  22. Yedidia MJ, Bickel J. Why aren't there more women leaders in academic medicine? tHe views of clinical department chairs. Acad Med. 2001;76(5):453465.
  23. Shin T. The gender gap in executive compensation: the role of female directors and chief executive officers. Ann Am Acad Pol Soc Sci. 2012(639):258278.
  24. Caniano DA, Sonnino RE, Paolo AM. Keys to career satisfaction: insights from a survey of women pediatric surgeons. J Pediatr Surg. 2004;39(6):984990.
  25. Sterne JA, White IR, Carlin JB, et al. Multiple imputation for missing data in epidemiological and clinical research: potential and pitfalls. BMJ. 2009;338:b2393.
  26. Imputation and Variance Estimation Software [computer program]. Ann Arbor, MI: Universtiy of Michigan; 2007.
  27. White IR, Royston P, Wood AM. Multiple Imputation using chained equations: issues and guidance for practice. Stat Med. 2010;30(4):377399.
  28. State of Hospital Medicine: 2010 Report Based on 2009 Data. Englewood, CO and Philadelphia, PA: Medical Group Management Association and Society of Hospital Medicine; 2010.
  29. Boulis AK, Jacobs JA. The Changing Face of Medicine: Women Doctors and the Evolution Of Health Care in America. Ithaca, NY: ILR Press/Cornell University Press; 2008.
  30. Babcock L, Laschever S. Women Don't Ask: Negotiation and the Gender Divide. Princeton, NJ: Princeton University Press; 2003.
  31. Sarfaty S, Kolb D, Barnett R, et al. Negotiation in academic medicine: a necessary career skill. J Womens Health (Larchmt). 2007;16(2):235244.
  32. Wade ME. Women and salary negotiation: the costs of self‐advocacy. Psychol Women Q. 2001;25:6576.
  33. State of Hospital Medicine: 2014 Report Based on 2013 Data. Englewood, CO and Philadelphia, PA: Medical Group Management Association and Society of Hospital Medicine; 2014.
  34. Isaac C, Lee B, Carnes M. Interventions that affect gender bias in hiring: a systematic review. Acad Med. 2009;84(10):14401446.
  35. Ley TJ, Hamilton BH. Sociology. The gender gap in NIH grant applications. Science. 2008;322(5907):14721474.
  36. Shollen SL, Bland CJ, Finstad DA, Taylor AL. Organizational climate and family life: how these factors affect the status of women faculty at one medical school. Acad Med. 2009;84(1):8794.
  37. Halperin TJ, Werler MM, Mulliken JB. Gender differences in the professional and private lives of plastic surgeons. Ann Plast Surg. 2010;64(6):775779.
  38. Wallace JE. Gender and supportive co‐worker relations in the medical profession. Gend Work Organ. 2014;21(1):117.
  39. Kaatz A, Carnes M. Stuck in the out‐group: Jennifer can't grow up, Jane's invisible, and Janet's over the hill. J Womens Health (Larchmt). 2014;23(6):481484.
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Hospitalists are a growing workforce numbering over 40,000 physicians, one‐third of whom are women.[1] Flexibility of work schedules and control over personal time have been the traditional selling points of the specialty.[2] Multiple studies of physician work life reveal growing physician dissatisfaction and a high prevalence of burnout.[3] To mitigate burnout risk, leaders in hospital medicine recognize the importance of creating a sustainable profession that offers both job and career satisfaction as well as work‐life balance and, importantly, fairness within the work environment.[4] Although success in some of these endeavors has been realized sporadically, sustaining work‐life balance and fairness in the specialty remains a work in progress, whereas evidence of high job attrition and pay inequities remain.[5, 6]

Pay inequity for women relative to men continues to be pervasive in medicine, including among early‐career physicians, researchers, and various specialists.[6, 7, 8, 9, 10, 11, 12, 13] The earnings gap seems to persist for physicians, even as federal efforts such as the Fair Pay Act of 2013 and the Paycheck Fairness Act of 2014 aim to end wage discrimination.[11, 14] Differences in specialty, part‐time status, and practice type do not mitigate the disparity.[8, 10, 15] Additional explanations have been proposed to explain the variability, including gender differences in negotiating skills, lack of opportunities to join networks of influence within organizations, and implicit or explicit bias and discrimination.[12, 16, 17, 18, 19, 20]

The earnings gap is also a consequence of what is commonly called the glass ceiling.[18, 19] Most agree that obstacles to fair advancement of women include absence of collaborative environments and role models who have successfully achieved work‐life balance.[17, 20, 21, 22] Somewhat surprisingly, women leaders in medicine seem to suffer greater income disparity than nonleaders; this income gap is prevalent among leaders in other elite professions as well.[7, 23] It is unknown whether women physicians' emphasis on work‐life balance, seen repeatedly in surveys, explains any of the pay disparity.[24] Little research to date has examined whether work‐life priorities of women in hospital medicine differ from men.

In this study, we sought to examine differences in job priorities between men and women hospitalists. In particular, we examine the relative prioritization of substantial pay to job satisfaction. We also examined gender differences in work patterns and earnings to explore potential sources of the persistent gender earnings gap.

METHODS

We analyzed data from the 20092010 Hospital Medicine Physician Worklife Survey, the design of which is detailed elsewhere.[4] Briefly, a 118‐item survey was administered by mail to a stratified sample of hospitalists from the Society of Hospital Medicine database and 3 large multisite hospitalist groups. A single survey item asked respondents to identify up to 4 out of 12 most important domains to their satisfaction with a hospitalist job. The domains were distilled from focus groups of nationally representative hospitalists as described previously,[4] and the survey item allowed up to one‐third of these domains to be identified as respondents' personal priorities. The list included: optimal variety of tasks, optimal workload, substantial pay, collegiality with other physicians, recognition by leaders, rewarding relationships with patients, satisfaction with nurses, optimal autonomy, control over personal time, fairness within organization, ample availability of resources to do job, and organizational climate of trust and belonging. We tabulated and ranked the frequency with which respondents selected each satisfaction domain by gender. Due to the nonstandard format of the survey item, we a priori decided to analyze only responses that were completed as instructed.

We also used demographic data including detailed work characteristics, clinical and nonclinical workload, total pretax earnings in 2009 as a hospitalist, and self‐identification as leader of their hospital medicine group. Respondent characteristics were tabulated and gender differences were tested using the t test, rank sum test, and the Fischer exact test as appropriate. We also listed the number of nonrespondents for each item. In estimating gender differences in earnings, we opted to use multiple‐imputation techniques to more conservatively account for greater variance inherent in the presence of missing data. Consistent with existing guidelines,[25] we demonstrated that item responses were not missing monotonically by visually inspecting patterns of nonresponse. We further demonstrated that data were missing at random by showing that response patterns of completed survey items did not predict whether or not a given variable response was missing using logistic regression models. We found no significant differences between respondents with complete and missing data. We verified that appropriate regression models for each variable on every other variable converged. We used Stata 13.1 (StataCorp, College Station, TX) to perform multiple imputations using chain equations (mi impute chain) to create 10 imputed tables for 7 normally distributed continuous variables using the ordinary least squares method, 3 non‐normally distributed variables using the predictive mean matching method, 2 nonordinal categorical variables using the multinomial logit method, and 1 binary variable using the logit method.[26, 27] Gender, pediatric specialty status, region of practice, and whether or not respondents prioritized substantial pay for job satisfaction were used as regular variables without missing data points.

Differences in earnings were assessed using a multivariate ordinary linear regression model applied to the imputed datasets fitted by forward selection of explanatory variables using P < 0.20 in bivariate analysis for inclusion and manual backward elimination of all statistically nonsignificant variables. We tested the significance of the women leader interaction term in the final parsimonious model. We used the usual significance threshold of P < 0.05 for inferences. Our analysis of publicly available anonymous data was exempt from IRB review.

RESULTS

Of the 816 survey respondents (response rate 25.6%), 40 either omitted the item soliciting work priorities or completed it incorrectly. Data from the remaining 776 respondents were used for the present analysis. Respondent characteristics are tabulated in Table 1. The characteristics of hospitalists by age, gender, specialty, practice model, and practice region were representative of US hospitalists from other surveys.[28]

Differences in Characteristics and Work Patterns of Women Compared to Men Hospitalists
 WomenMenP ValueNo. of Missing Responses
  • NOTE: Abbreviations: DP, domestic partnership; FTE, full‐time equivalent; IQR, interquartile range; SD, standard deviation.

No.263513 0
Role, n (%)  <0.010
Frontline hospitalist201 (76)337 (66)  
Hospitalist leader53 (24)176 (34)  
Age, y, mean (SD)42 (8)45 (9)<0.0167
Years in current job, mean (SD)5 (4)6 (5)0.0714
Specialty, n (%)  <0.010
Internal medicine160 (61)369 (72)  
Pediatrics56 (21)57 (11)  
Other39 (15)47 (9)  
Family medicine8 (3)40 (8)  
Practice model, n (%)  0.0219
Hospital employed110 (43)227 (46)  
Multispecialty group44 (17)68 (14)  
University/medical school47 (18)58 (12)  
Multistate group27 (11)73 (15)  
Local hospitalist group22 (8)65 (13)  
Other7 (3)9 (2)  
Practice region, n (%)  0.140
Southeast56 (21)151 (29)  
Midwest58 (22)106 (21)  
Northeast54 (21)96 (19)  
Southwest44 (17)83 (16)  
West51 (19)77 (15)  
Full‐time equivalents, n (%)  <0.0142
<100%46 (18)60 (12)  
100%202 (81)402 (83)  
>100%2 (1)22 (5)  
Days per month doing clinical work if FTE 100%, median (IQR)15 (1418)16 (1420)0.1211
Hours per day doing clinical work, median (IQR)11 (912)11 (912)0.6730
Consecutive days doing clinical work, median (IQR)7 (57)7 (57)0.9417
Percentage of work at night, median (IQR)15 (530)15 (525)0.4516
Percentage of night work in hospital if working nights, median (IQR)100 (5100)100 (10100)0.128
Hours per month doing nonclinical work, median (IQR)12 (540)15 (540)0.7726
Estimated daily billable encounters, mean (IQR)14 (1116)15 (1218)0.0154
Total earnings in fiscal year 2009, median US$1,000 (IQR)185 (150210)202 (180240)<0.0156
Marriage/domestic partnership status, n (%)  0.1543
Married/currently in DP197 (80)421 (86)  
Never married/never in DP26 (11)42 (9)  
Divorced or separated18 (7)20 (4)  
Other4 (2)5 (1)  
Dependent children under 7 years old living in home, n (%)  0.2242
0136 (55)265 (54)  
147 (19)92 (19)  
252 (21)87 (18)  
312 (5)43 (9)  

Several gender differences were seen in the characteristics of hospitalists and their work (Table 1). Women compared to men hospitalists were less likely to be leaders, more likely to be pediatricians, work in university settings, and practice in Western states. Women compared to men, on average, were younger by 3 years, worked fewer full‐time equivalents (FTEs), worked a greater percentage of nights, and reported fewer billable encounters per shift. They were also more likely to be divorced or separated.

Job satisfaction priorities differed for women and men hospitalists. Table 2 lists job satisfaction domains in descending order of the frequency prioritized by men. The largest proportion of women and men prioritized optimal workload. However, although substantial pay was prioritized next most frequently by men, more women prioritized collegiality and control over personal time than substantial pay.

Percentage of Women and Men Who Indicated That a Domain Was One of Up to Four Most Important Factors to Her/His Job Satisfaction
 Women, %RankMen, %Rank
Optimal workload591591
Substantial pay414502
Control over personal time443413
Collegiality with physicians472384
Rewarding relationships with patients355345
Organizational climate of trust and belonging277336
Ample availability of resources to do job249277
Optimal autonomy268248
Fairness within organization1510239
Optimal variety of tasks2962210
Recognition by leaders11121011
Satisfaction with nurses1211712

Key differences in individual characteristics, work patterns, and indicating substantial pay as a priority were associated with self‐reported total earnings in 2009 from respondents' work as a hospitalist. As shown in Table 3, the inclusion of detailed productivity measures such as FTE, days of monthly clinical work, and estimated number of daily billable encounters yielded a model that explained 33% of variance in earnings. After adjusting for significant covariates including pediatric specialty, practice model, geography, and amount and type of clinical work, the estimated underpayment of women compared to men was $14,581. Hospitalists who prioritized substantial pay earned $10,771 more than those who did not. The female x leader interaction term testing the hypothesis that gender disparity is greater among leaders than frontline hospitalists was not statistically significant ($16,720, P = 0.087) and excluded from the final model.

Ordinary Linear Regression Model Incorporating Multiple Imputation Estimates to Examine Adjusted Gender Differences in Hospitalists' Self‐Reported Earnings in 2009 US Dollars
 Differences in Salary, 2009 US$ (95% CI)P Value
  • NOTE: Abbreviations: CI, confidence interval; FTE, full‐time equivalent.

Women14,581 (23,074 to 6,089)<0.01
Leader21,997 (13,313 to 30,682)<0.01
Prioritized substantial pay10,771 (2,651 to 18,891)<0.01
Pediatric specialty31,126 (43,007 to 19,244)<0.01
Practice model  
Hospital employedREF 
Multispecialty group1,922 (13,891 to 10,047)0.75
University/medical school33,503 (46,336 to 20,671)<0.01
Multistate group6,505 (72,69 to 20,279)0.35
Local hospitalist group9,330 (4,352 to 23,012)0.18
Other17,364 (45,741 to 11,012)0.23
Practice region  
SoutheastREF 
Midwest1,225 (10,595 to 13,044)0.84
Northeast15,712 (28,182 to 3,242)0.01
Southwest722 (13,545 to 12,101)0.91
West5,251 (7,383 to 17,885)0.41
FTE1,021 (762 to 1,279)<0.01
Days per month doing clinical work1,209 (443 to 1,975)<0.01
Estimated daily billable encounters608 (20 to 1,196)0.04

DISCUSSION

In a national stratified sample of US hospitalists, we found gender differences in job satisfaction priorities and hospitalist work characteristics. We also confirmed the persistence of a substantial gender earnings disparity. Lower earnings among women compared to men hospitalists were present in our data after controlling for age, pediatric specialty, practice model, geography, type of clinical work, and productivity measures. The gender earnings disparity noted in 1999[6] persists, although it appears to have decreased, possibly indicating progress toward equity. We showed that women hospitalists' relative tendency not to prioritize pay explains a significant portion of the residual income gap.

Hoff examined hospitalist earnings in a large national survey of hospitalists in 1999. Our cohorts differed in age and experience (both lower in the Hoff study). An estimated $24,000 ($124,266 vs. $148,132) earnings gap between women and men was greater than our estimate of $14,581 following an interval of 10 years. Although survey items differed, both studies found that women were less interested in pay than men when considering a hospitalist job. Hoff also found that work setting and attitudes about pay and lifestyle were significantly related to earnings. We extended the previous analyses of gender differences in job satisfaction priorities, work, and demographic characteristics to explain the earnings gap and understand how it may be remedied.

When considering job satisfaction, we found that more men than women prioritized substantial pay and that prioritization of substantial pay was directly related to higher earnings. Therefore, fewer women prioritizing pay partly explains women's lower earnings. Reasons for why fewer women prioritize pay were not assessed in this study but may include factors like being part of 2‐income households and competing commitments.[29] Priorities may even be influenced by empirically observed gender differences in discussions of financial matters, governed by cultural norms. Such norms may implicitly sanction employers to offer women less pay than men for the same or similar work. Women may disadvantage themselves by negotiating less or less well than men for higher starting and promotion salaries. They may be perceived more negatively than men when they do negotiate pay, leading to unintended negative consequences such as loss of social networks, decreased likability, and even loss of job offers.[29, 30, 31, 32]

More women prioritized optimal variety of tasks (6th most prevalent among women and 10th among men). Women who highly rate optimal variety of tasks as a job satisfier may choose positions in which they teach, perform research, and participate in hospital committees and quality‐improvement work, but offer lower pay. Yet hours per month doing nonclinical work was not significantly different between men and women, nor associated with earnings differences in our earnings models. Understanding whether women self‐select into hospitalist jobs with like‐minded colleagues to achieve complementary fit or end up supplementing their skills with hospitalists with different priorities may inform strategies to reduce the gender income disparity.[5] Unlike disparities between various hospital medicine groups, systematic disparities within practices risk generating low levels of organizational fairness and burnout among employees.

Not surprisingly, productivity was positively associated with earnings but did not fully account for the gender earnings gap. Our data demonstrated that women, on average, were associated with work characteristics that expectedly generate less compensation. For example, women were younger, more often part time, academic, pediatric, less often leaders, and reported fewer billable encounters compared to men. These differences account for some of the earnings gap between men and women, but these factors were controlled for in the earnings model. In addition, our analysis may have underestimated the gap by not incorporating loss of fringe benefits from part‐time status and not comprehensively counting incentive pay associated with high productivity. Other work patterns more commonly associated with women suggest an imbalance in reimbursement. More women than men work nights that are often compensated at higher rates than daytime work, yet their average pay was less, suggesting that compensation for night work may need to be adjusted to reflect its unique burdens and responsibilities.[33]

Although the gender pay gap was not more extreme among leaders compared to frontline hospitalists in our data, the trend, nonetheless, underscores an important consideration. Whereas clinical work is paid for in mostly measurable ways, pay for leadership may be influenced by intangible factors such as reputation, negotiation, and confidence that may disadvantage women relative to men.[7, 19, 23, 34, 35, 36] Efforts to overcome implicit gender bias should be most effective when we consciously couple fair promotion of women to leadership with fair compensation commensurate with their male peers.[21]

Our data are vulnerable to nonresponse bias.[1, 4, 5] Post hoc analyses demonstrated that distributions of age, gender, practice model and region of our respondents were similar to other nationally representative cohorts of hospitalists. Consequently, we believe our data can make valid estimates about a nationally representative sample of hospitalists. However, we acknowledge several additional weaknesses of self‐reported data, including recall bias and accuracy of productivity figures, which were rounded to variable significant digits by respondents. Earnings analysis using this data was intended to be exploratory, but the findings echoed analyses using more authoritative data sources.[11] Still, we made inferences conservatively by adopting multiple imputation techniques for dealing with nonresponse surveys in adherence to established reporting guidelines.[25] We also note several limitations relevant to multiple imputations. The greater prevalence of missing data for survey items soliciting earnings and the number of billable encounters suggest they were not truly missing at random as assumed. However, we showed that missingness is unrelated to the variables under study, justifying use of the technique. The wider measures of variance derived from multiple imputations make us vulnerable to not detecting associations that may exist.

The gender earnings gap found in hospital medicine echoes the gap found in multiple medical specialties, including but not limited to pediatrics, academic medicine, gastroenterology, and plastic surgery.[7, 8, 9, 11, 12, 13, 37] Hospital medicine employment models and practice patterns have important structural differences compared to previously studied populations that could mitigate factors contributing to women physicians' lower earnings. However, despite well‐defined working hours, lack of control over the number of patient encounters per day and high prevalence of hospital‐employed practice models, the gender earnings gap persists. We showed that lower prioritization for pay may reflect the self‐selection of women into lower paying jobs. Unmeasured factors, including implicit bias and differences in negotiations, social networks and mentoring opportunities[38, 39] may also contribute to pay differences between men and women hospitalists. As hospital medicine tackles gender inequities and other disparities, strategies to assess and address fair physician compensation must be on the table.

Hospitalists are a growing workforce numbering over 40,000 physicians, one‐third of whom are women.[1] Flexibility of work schedules and control over personal time have been the traditional selling points of the specialty.[2] Multiple studies of physician work life reveal growing physician dissatisfaction and a high prevalence of burnout.[3] To mitigate burnout risk, leaders in hospital medicine recognize the importance of creating a sustainable profession that offers both job and career satisfaction as well as work‐life balance and, importantly, fairness within the work environment.[4] Although success in some of these endeavors has been realized sporadically, sustaining work‐life balance and fairness in the specialty remains a work in progress, whereas evidence of high job attrition and pay inequities remain.[5, 6]

Pay inequity for women relative to men continues to be pervasive in medicine, including among early‐career physicians, researchers, and various specialists.[6, 7, 8, 9, 10, 11, 12, 13] The earnings gap seems to persist for physicians, even as federal efforts such as the Fair Pay Act of 2013 and the Paycheck Fairness Act of 2014 aim to end wage discrimination.[11, 14] Differences in specialty, part‐time status, and practice type do not mitigate the disparity.[8, 10, 15] Additional explanations have been proposed to explain the variability, including gender differences in negotiating skills, lack of opportunities to join networks of influence within organizations, and implicit or explicit bias and discrimination.[12, 16, 17, 18, 19, 20]

The earnings gap is also a consequence of what is commonly called the glass ceiling.[18, 19] Most agree that obstacles to fair advancement of women include absence of collaborative environments and role models who have successfully achieved work‐life balance.[17, 20, 21, 22] Somewhat surprisingly, women leaders in medicine seem to suffer greater income disparity than nonleaders; this income gap is prevalent among leaders in other elite professions as well.[7, 23] It is unknown whether women physicians' emphasis on work‐life balance, seen repeatedly in surveys, explains any of the pay disparity.[24] Little research to date has examined whether work‐life priorities of women in hospital medicine differ from men.

In this study, we sought to examine differences in job priorities between men and women hospitalists. In particular, we examine the relative prioritization of substantial pay to job satisfaction. We also examined gender differences in work patterns and earnings to explore potential sources of the persistent gender earnings gap.

METHODS

We analyzed data from the 20092010 Hospital Medicine Physician Worklife Survey, the design of which is detailed elsewhere.[4] Briefly, a 118‐item survey was administered by mail to a stratified sample of hospitalists from the Society of Hospital Medicine database and 3 large multisite hospitalist groups. A single survey item asked respondents to identify up to 4 out of 12 most important domains to their satisfaction with a hospitalist job. The domains were distilled from focus groups of nationally representative hospitalists as described previously,[4] and the survey item allowed up to one‐third of these domains to be identified as respondents' personal priorities. The list included: optimal variety of tasks, optimal workload, substantial pay, collegiality with other physicians, recognition by leaders, rewarding relationships with patients, satisfaction with nurses, optimal autonomy, control over personal time, fairness within organization, ample availability of resources to do job, and organizational climate of trust and belonging. We tabulated and ranked the frequency with which respondents selected each satisfaction domain by gender. Due to the nonstandard format of the survey item, we a priori decided to analyze only responses that were completed as instructed.

We also used demographic data including detailed work characteristics, clinical and nonclinical workload, total pretax earnings in 2009 as a hospitalist, and self‐identification as leader of their hospital medicine group. Respondent characteristics were tabulated and gender differences were tested using the t test, rank sum test, and the Fischer exact test as appropriate. We also listed the number of nonrespondents for each item. In estimating gender differences in earnings, we opted to use multiple‐imputation techniques to more conservatively account for greater variance inherent in the presence of missing data. Consistent with existing guidelines,[25] we demonstrated that item responses were not missing monotonically by visually inspecting patterns of nonresponse. We further demonstrated that data were missing at random by showing that response patterns of completed survey items did not predict whether or not a given variable response was missing using logistic regression models. We found no significant differences between respondents with complete and missing data. We verified that appropriate regression models for each variable on every other variable converged. We used Stata 13.1 (StataCorp, College Station, TX) to perform multiple imputations using chain equations (mi impute chain) to create 10 imputed tables for 7 normally distributed continuous variables using the ordinary least squares method, 3 non‐normally distributed variables using the predictive mean matching method, 2 nonordinal categorical variables using the multinomial logit method, and 1 binary variable using the logit method.[26, 27] Gender, pediatric specialty status, region of practice, and whether or not respondents prioritized substantial pay for job satisfaction were used as regular variables without missing data points.

Differences in earnings were assessed using a multivariate ordinary linear regression model applied to the imputed datasets fitted by forward selection of explanatory variables using P < 0.20 in bivariate analysis for inclusion and manual backward elimination of all statistically nonsignificant variables. We tested the significance of the women leader interaction term in the final parsimonious model. We used the usual significance threshold of P < 0.05 for inferences. Our analysis of publicly available anonymous data was exempt from IRB review.

RESULTS

Of the 816 survey respondents (response rate 25.6%), 40 either omitted the item soliciting work priorities or completed it incorrectly. Data from the remaining 776 respondents were used for the present analysis. Respondent characteristics are tabulated in Table 1. The characteristics of hospitalists by age, gender, specialty, practice model, and practice region were representative of US hospitalists from other surveys.[28]

Differences in Characteristics and Work Patterns of Women Compared to Men Hospitalists
 WomenMenP ValueNo. of Missing Responses
  • NOTE: Abbreviations: DP, domestic partnership; FTE, full‐time equivalent; IQR, interquartile range; SD, standard deviation.

No.263513 0
Role, n (%)  <0.010
Frontline hospitalist201 (76)337 (66)  
Hospitalist leader53 (24)176 (34)  
Age, y, mean (SD)42 (8)45 (9)<0.0167
Years in current job, mean (SD)5 (4)6 (5)0.0714
Specialty, n (%)  <0.010
Internal medicine160 (61)369 (72)  
Pediatrics56 (21)57 (11)  
Other39 (15)47 (9)  
Family medicine8 (3)40 (8)  
Practice model, n (%)  0.0219
Hospital employed110 (43)227 (46)  
Multispecialty group44 (17)68 (14)  
University/medical school47 (18)58 (12)  
Multistate group27 (11)73 (15)  
Local hospitalist group22 (8)65 (13)  
Other7 (3)9 (2)  
Practice region, n (%)  0.140
Southeast56 (21)151 (29)  
Midwest58 (22)106 (21)  
Northeast54 (21)96 (19)  
Southwest44 (17)83 (16)  
West51 (19)77 (15)  
Full‐time equivalents, n (%)  <0.0142
<100%46 (18)60 (12)  
100%202 (81)402 (83)  
>100%2 (1)22 (5)  
Days per month doing clinical work if FTE 100%, median (IQR)15 (1418)16 (1420)0.1211
Hours per day doing clinical work, median (IQR)11 (912)11 (912)0.6730
Consecutive days doing clinical work, median (IQR)7 (57)7 (57)0.9417
Percentage of work at night, median (IQR)15 (530)15 (525)0.4516
Percentage of night work in hospital if working nights, median (IQR)100 (5100)100 (10100)0.128
Hours per month doing nonclinical work, median (IQR)12 (540)15 (540)0.7726
Estimated daily billable encounters, mean (IQR)14 (1116)15 (1218)0.0154
Total earnings in fiscal year 2009, median US$1,000 (IQR)185 (150210)202 (180240)<0.0156
Marriage/domestic partnership status, n (%)  0.1543
Married/currently in DP197 (80)421 (86)  
Never married/never in DP26 (11)42 (9)  
Divorced or separated18 (7)20 (4)  
Other4 (2)5 (1)  
Dependent children under 7 years old living in home, n (%)  0.2242
0136 (55)265 (54)  
147 (19)92 (19)  
252 (21)87 (18)  
312 (5)43 (9)  

Several gender differences were seen in the characteristics of hospitalists and their work (Table 1). Women compared to men hospitalists were less likely to be leaders, more likely to be pediatricians, work in university settings, and practice in Western states. Women compared to men, on average, were younger by 3 years, worked fewer full‐time equivalents (FTEs), worked a greater percentage of nights, and reported fewer billable encounters per shift. They were also more likely to be divorced or separated.

Job satisfaction priorities differed for women and men hospitalists. Table 2 lists job satisfaction domains in descending order of the frequency prioritized by men. The largest proportion of women and men prioritized optimal workload. However, although substantial pay was prioritized next most frequently by men, more women prioritized collegiality and control over personal time than substantial pay.

Percentage of Women and Men Who Indicated That a Domain Was One of Up to Four Most Important Factors to Her/His Job Satisfaction
 Women, %RankMen, %Rank
Optimal workload591591
Substantial pay414502
Control over personal time443413
Collegiality with physicians472384
Rewarding relationships with patients355345
Organizational climate of trust and belonging277336
Ample availability of resources to do job249277
Optimal autonomy268248
Fairness within organization1510239
Optimal variety of tasks2962210
Recognition by leaders11121011
Satisfaction with nurses1211712

Key differences in individual characteristics, work patterns, and indicating substantial pay as a priority were associated with self‐reported total earnings in 2009 from respondents' work as a hospitalist. As shown in Table 3, the inclusion of detailed productivity measures such as FTE, days of monthly clinical work, and estimated number of daily billable encounters yielded a model that explained 33% of variance in earnings. After adjusting for significant covariates including pediatric specialty, practice model, geography, and amount and type of clinical work, the estimated underpayment of women compared to men was $14,581. Hospitalists who prioritized substantial pay earned $10,771 more than those who did not. The female x leader interaction term testing the hypothesis that gender disparity is greater among leaders than frontline hospitalists was not statistically significant ($16,720, P = 0.087) and excluded from the final model.

Ordinary Linear Regression Model Incorporating Multiple Imputation Estimates to Examine Adjusted Gender Differences in Hospitalists' Self‐Reported Earnings in 2009 US Dollars
 Differences in Salary, 2009 US$ (95% CI)P Value
  • NOTE: Abbreviations: CI, confidence interval; FTE, full‐time equivalent.

Women14,581 (23,074 to 6,089)<0.01
Leader21,997 (13,313 to 30,682)<0.01
Prioritized substantial pay10,771 (2,651 to 18,891)<0.01
Pediatric specialty31,126 (43,007 to 19,244)<0.01
Practice model  
Hospital employedREF 
Multispecialty group1,922 (13,891 to 10,047)0.75
University/medical school33,503 (46,336 to 20,671)<0.01
Multistate group6,505 (72,69 to 20,279)0.35
Local hospitalist group9,330 (4,352 to 23,012)0.18
Other17,364 (45,741 to 11,012)0.23
Practice region  
SoutheastREF 
Midwest1,225 (10,595 to 13,044)0.84
Northeast15,712 (28,182 to 3,242)0.01
Southwest722 (13,545 to 12,101)0.91
West5,251 (7,383 to 17,885)0.41
FTE1,021 (762 to 1,279)<0.01
Days per month doing clinical work1,209 (443 to 1,975)<0.01
Estimated daily billable encounters608 (20 to 1,196)0.04

DISCUSSION

In a national stratified sample of US hospitalists, we found gender differences in job satisfaction priorities and hospitalist work characteristics. We also confirmed the persistence of a substantial gender earnings disparity. Lower earnings among women compared to men hospitalists were present in our data after controlling for age, pediatric specialty, practice model, geography, type of clinical work, and productivity measures. The gender earnings disparity noted in 1999[6] persists, although it appears to have decreased, possibly indicating progress toward equity. We showed that women hospitalists' relative tendency not to prioritize pay explains a significant portion of the residual income gap.

Hoff examined hospitalist earnings in a large national survey of hospitalists in 1999. Our cohorts differed in age and experience (both lower in the Hoff study). An estimated $24,000 ($124,266 vs. $148,132) earnings gap between women and men was greater than our estimate of $14,581 following an interval of 10 years. Although survey items differed, both studies found that women were less interested in pay than men when considering a hospitalist job. Hoff also found that work setting and attitudes about pay and lifestyle were significantly related to earnings. We extended the previous analyses of gender differences in job satisfaction priorities, work, and demographic characteristics to explain the earnings gap and understand how it may be remedied.

When considering job satisfaction, we found that more men than women prioritized substantial pay and that prioritization of substantial pay was directly related to higher earnings. Therefore, fewer women prioritizing pay partly explains women's lower earnings. Reasons for why fewer women prioritize pay were not assessed in this study but may include factors like being part of 2‐income households and competing commitments.[29] Priorities may even be influenced by empirically observed gender differences in discussions of financial matters, governed by cultural norms. Such norms may implicitly sanction employers to offer women less pay than men for the same or similar work. Women may disadvantage themselves by negotiating less or less well than men for higher starting and promotion salaries. They may be perceived more negatively than men when they do negotiate pay, leading to unintended negative consequences such as loss of social networks, decreased likability, and even loss of job offers.[29, 30, 31, 32]

More women prioritized optimal variety of tasks (6th most prevalent among women and 10th among men). Women who highly rate optimal variety of tasks as a job satisfier may choose positions in which they teach, perform research, and participate in hospital committees and quality‐improvement work, but offer lower pay. Yet hours per month doing nonclinical work was not significantly different between men and women, nor associated with earnings differences in our earnings models. Understanding whether women self‐select into hospitalist jobs with like‐minded colleagues to achieve complementary fit or end up supplementing their skills with hospitalists with different priorities may inform strategies to reduce the gender income disparity.[5] Unlike disparities between various hospital medicine groups, systematic disparities within practices risk generating low levels of organizational fairness and burnout among employees.

Not surprisingly, productivity was positively associated with earnings but did not fully account for the gender earnings gap. Our data demonstrated that women, on average, were associated with work characteristics that expectedly generate less compensation. For example, women were younger, more often part time, academic, pediatric, less often leaders, and reported fewer billable encounters compared to men. These differences account for some of the earnings gap between men and women, but these factors were controlled for in the earnings model. In addition, our analysis may have underestimated the gap by not incorporating loss of fringe benefits from part‐time status and not comprehensively counting incentive pay associated with high productivity. Other work patterns more commonly associated with women suggest an imbalance in reimbursement. More women than men work nights that are often compensated at higher rates than daytime work, yet their average pay was less, suggesting that compensation for night work may need to be adjusted to reflect its unique burdens and responsibilities.[33]

Although the gender pay gap was not more extreme among leaders compared to frontline hospitalists in our data, the trend, nonetheless, underscores an important consideration. Whereas clinical work is paid for in mostly measurable ways, pay for leadership may be influenced by intangible factors such as reputation, negotiation, and confidence that may disadvantage women relative to men.[7, 19, 23, 34, 35, 36] Efforts to overcome implicit gender bias should be most effective when we consciously couple fair promotion of women to leadership with fair compensation commensurate with their male peers.[21]

Our data are vulnerable to nonresponse bias.[1, 4, 5] Post hoc analyses demonstrated that distributions of age, gender, practice model and region of our respondents were similar to other nationally representative cohorts of hospitalists. Consequently, we believe our data can make valid estimates about a nationally representative sample of hospitalists. However, we acknowledge several additional weaknesses of self‐reported data, including recall bias and accuracy of productivity figures, which were rounded to variable significant digits by respondents. Earnings analysis using this data was intended to be exploratory, but the findings echoed analyses using more authoritative data sources.[11] Still, we made inferences conservatively by adopting multiple imputation techniques for dealing with nonresponse surveys in adherence to established reporting guidelines.[25] We also note several limitations relevant to multiple imputations. The greater prevalence of missing data for survey items soliciting earnings and the number of billable encounters suggest they were not truly missing at random as assumed. However, we showed that missingness is unrelated to the variables under study, justifying use of the technique. The wider measures of variance derived from multiple imputations make us vulnerable to not detecting associations that may exist.

The gender earnings gap found in hospital medicine echoes the gap found in multiple medical specialties, including but not limited to pediatrics, academic medicine, gastroenterology, and plastic surgery.[7, 8, 9, 11, 12, 13, 37] Hospital medicine employment models and practice patterns have important structural differences compared to previously studied populations that could mitigate factors contributing to women physicians' lower earnings. However, despite well‐defined working hours, lack of control over the number of patient encounters per day and high prevalence of hospital‐employed practice models, the gender earnings gap persists. We showed that lower prioritization for pay may reflect the self‐selection of women into lower paying jobs. Unmeasured factors, including implicit bias and differences in negotiations, social networks and mentoring opportunities[38, 39] may also contribute to pay differences between men and women hospitalists. As hospital medicine tackles gender inequities and other disparities, strategies to assess and address fair physician compensation must be on the table.

References
  1. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB; Society of Hospital Medicine Career Satisfaction Task F. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7(5):402410.
  2. Wachter RM, Goldman L. The emerging role of “hospitalists” in the American health care system. N Engl J Med. 1996;335(7):514517.
  3. Linzer M, Baier Manwell L, Mundt M, et al. Organizational climate, stress, and error in primary care: The MEMO study. In: Henriksen K, Battles JB, Marks ES, Lewin DI, eds. Advances in Patient Safety: From Research to Implementation. Vol. 1. Research Findings. Rockville, MD; Agency for Healthcare Research and Quality; 2005.
  4. Hinami K, Whelan CT, Wolosin RJ, Miller JA, Wetterneck TB. Worklife and satisfaction of hospitalists: toward flourishing careers. J Gen Intern Med. 2012;27(1):2836.
  5. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB. Person‐job fit: an exploratory cross‐sectional analysis of hospitalists. J Hosp Med. 2013;8(2):96101.
  6. Hoff TJ. Doing the same and earning less: male and female physicians in a new medical specialty. Inquiry. 2004;41(3):301315.
  7. Ash AS, Carr PL, Goldstein R, Friedman RH. Compensation and advancement of women in academic medicine: Is there equity? Ann Intern Med. 2004;141(3):205212.
  8. Baker LC. Differences in earnings between male and female physicians. N Engl J Med. 1996;334(15):960964.
  9. Jagsi R, Griffith KA, Stewart A, Sambuco D, DeCastro R, Ubel PA. Gender differences in the salaries of physician researchers. JAMA. 2012;307(22):24102417.
  10. McMurray JE, Linzer M, Konrad TR, Douglas J, Shugerman R, Nelson K. The work lives of women physicians results from the physician work life study. The SGIM Career Satisfaction Study Group. J Gen Intern Med. 2000;15(6):372380.
  11. Sasso AT, Richards MR, Chou CF, Gerber SE. The $16,819 pay gap for newly trained physicians: the unexplained trend of men earning more than women. Health Aff (Millwood). 2011;30(2):193201.
  12. Rotbart HA, McMillen D, Taussig H, Daniels SR. Assessing gender equity in a large academic department of pediatrics. Acad Med. 2012;87(1):98104.
  13. Burke CA, Sastri SV, Jacobsen G, Arlow FL, Karlstadt RG, Raymond P. Gender disparity in the practice of gastroenterology: the first 5 years of a career. Am J Gastroenterol. 2005;100(2):259264.
  14. H.R. 438, Fair Pay Act of 2013. 113th Congress (2013‐2014).
  15. Tracy EE, Wiler JL, Holschen JC, Patel SS, Ligda KO. Topics to ponder: part‐time practice and pay parity. Gend Med. 2010;7(4):350356.
  16. Carey EC, Weissman DE. Understanding and finding mentorship: a review for junior faculty. J Palliat Med. 2010;13(11):13731379.
  17. Fried LP, Francomano CA, MacDonald SM, et al. Career development for women in academic medicine: Multiple interventions in a department of medicine. JAMA. 1996;276(11):898905.
  18. Kaplan SH, Sullivan LM, Dukes KA, Phillips CF, Kelch RP, Schaller JG. Sex differences in academic advancement. Results of a national study of pediatricians. N Engl J Med. 1996;335(17):12821289.
  19. Tesch BJ, Wood HM, Helwig AL, Nattinger AB. Promotion of women physicians in academic medicine. Glass ceiling or sticky floor? JAMA. 1995;273(13):10221025.
  20. Levine RB, Lin F, Kern DE, Wright SM, Carrese J. Stories from early‐career women physicians who have left academic medicine: a qualitative study at a single institution. Acad Med. 2011;86(6):752758.
  21. Pololi LH, Civian JT, Brennan RT, Dottolo AL, Krupat E. Experiencing the culture of academic medicine: gender matters, a national study. J Gen Intern Med. 2013;28(2):201207.
  22. Yedidia MJ, Bickel J. Why aren't there more women leaders in academic medicine? tHe views of clinical department chairs. Acad Med. 2001;76(5):453465.
  23. Shin T. The gender gap in executive compensation: the role of female directors and chief executive officers. Ann Am Acad Pol Soc Sci. 2012(639):258278.
  24. Caniano DA, Sonnino RE, Paolo AM. Keys to career satisfaction: insights from a survey of women pediatric surgeons. J Pediatr Surg. 2004;39(6):984990.
  25. Sterne JA, White IR, Carlin JB, et al. Multiple imputation for missing data in epidemiological and clinical research: potential and pitfalls. BMJ. 2009;338:b2393.
  26. Imputation and Variance Estimation Software [computer program]. Ann Arbor, MI: Universtiy of Michigan; 2007.
  27. White IR, Royston P, Wood AM. Multiple Imputation using chained equations: issues and guidance for practice. Stat Med. 2010;30(4):377399.
  28. State of Hospital Medicine: 2010 Report Based on 2009 Data. Englewood, CO and Philadelphia, PA: Medical Group Management Association and Society of Hospital Medicine; 2010.
  29. Boulis AK, Jacobs JA. The Changing Face of Medicine: Women Doctors and the Evolution Of Health Care in America. Ithaca, NY: ILR Press/Cornell University Press; 2008.
  30. Babcock L, Laschever S. Women Don't Ask: Negotiation and the Gender Divide. Princeton, NJ: Princeton University Press; 2003.
  31. Sarfaty S, Kolb D, Barnett R, et al. Negotiation in academic medicine: a necessary career skill. J Womens Health (Larchmt). 2007;16(2):235244.
  32. Wade ME. Women and salary negotiation: the costs of self‐advocacy. Psychol Women Q. 2001;25:6576.
  33. State of Hospital Medicine: 2014 Report Based on 2013 Data. Englewood, CO and Philadelphia, PA: Medical Group Management Association and Society of Hospital Medicine; 2014.
  34. Isaac C, Lee B, Carnes M. Interventions that affect gender bias in hiring: a systematic review. Acad Med. 2009;84(10):14401446.
  35. Ley TJ, Hamilton BH. Sociology. The gender gap in NIH grant applications. Science. 2008;322(5907):14721474.
  36. Shollen SL, Bland CJ, Finstad DA, Taylor AL. Organizational climate and family life: how these factors affect the status of women faculty at one medical school. Acad Med. 2009;84(1):8794.
  37. Halperin TJ, Werler MM, Mulliken JB. Gender differences in the professional and private lives of plastic surgeons. Ann Plast Surg. 2010;64(6):775779.
  38. Wallace JE. Gender and supportive co‐worker relations in the medical profession. Gend Work Organ. 2014;21(1):117.
  39. Kaatz A, Carnes M. Stuck in the out‐group: Jennifer can't grow up, Jane's invisible, and Janet's over the hill. J Womens Health (Larchmt). 2014;23(6):481484.
References
  1. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB; Society of Hospital Medicine Career Satisfaction Task F. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7(5):402410.
  2. Wachter RM, Goldman L. The emerging role of “hospitalists” in the American health care system. N Engl J Med. 1996;335(7):514517.
  3. Linzer M, Baier Manwell L, Mundt M, et al. Organizational climate, stress, and error in primary care: The MEMO study. In: Henriksen K, Battles JB, Marks ES, Lewin DI, eds. Advances in Patient Safety: From Research to Implementation. Vol. 1. Research Findings. Rockville, MD; Agency for Healthcare Research and Quality; 2005.
  4. Hinami K, Whelan CT, Wolosin RJ, Miller JA, Wetterneck TB. Worklife and satisfaction of hospitalists: toward flourishing careers. J Gen Intern Med. 2012;27(1):2836.
  5. Hinami K, Whelan CT, Miller JA, Wolosin RJ, Wetterneck TB. Person‐job fit: an exploratory cross‐sectional analysis of hospitalists. J Hosp Med. 2013;8(2):96101.
  6. Hoff TJ. Doing the same and earning less: male and female physicians in a new medical specialty. Inquiry. 2004;41(3):301315.
  7. Ash AS, Carr PL, Goldstein R, Friedman RH. Compensation and advancement of women in academic medicine: Is there equity? Ann Intern Med. 2004;141(3):205212.
  8. Baker LC. Differences in earnings between male and female physicians. N Engl J Med. 1996;334(15):960964.
  9. Jagsi R, Griffith KA, Stewart A, Sambuco D, DeCastro R, Ubel PA. Gender differences in the salaries of physician researchers. JAMA. 2012;307(22):24102417.
  10. McMurray JE, Linzer M, Konrad TR, Douglas J, Shugerman R, Nelson K. The work lives of women physicians results from the physician work life study. The SGIM Career Satisfaction Study Group. J Gen Intern Med. 2000;15(6):372380.
  11. Sasso AT, Richards MR, Chou CF, Gerber SE. The $16,819 pay gap for newly trained physicians: the unexplained trend of men earning more than women. Health Aff (Millwood). 2011;30(2):193201.
  12. Rotbart HA, McMillen D, Taussig H, Daniels SR. Assessing gender equity in a large academic department of pediatrics. Acad Med. 2012;87(1):98104.
  13. Burke CA, Sastri SV, Jacobsen G, Arlow FL, Karlstadt RG, Raymond P. Gender disparity in the practice of gastroenterology: the first 5 years of a career. Am J Gastroenterol. 2005;100(2):259264.
  14. H.R. 438, Fair Pay Act of 2013. 113th Congress (2013‐2014).
  15. Tracy EE, Wiler JL, Holschen JC, Patel SS, Ligda KO. Topics to ponder: part‐time practice and pay parity. Gend Med. 2010;7(4):350356.
  16. Carey EC, Weissman DE. Understanding and finding mentorship: a review for junior faculty. J Palliat Med. 2010;13(11):13731379.
  17. Fried LP, Francomano CA, MacDonald SM, et al. Career development for women in academic medicine: Multiple interventions in a department of medicine. JAMA. 1996;276(11):898905.
  18. Kaplan SH, Sullivan LM, Dukes KA, Phillips CF, Kelch RP, Schaller JG. Sex differences in academic advancement. Results of a national study of pediatricians. N Engl J Med. 1996;335(17):12821289.
  19. Tesch BJ, Wood HM, Helwig AL, Nattinger AB. Promotion of women physicians in academic medicine. Glass ceiling or sticky floor? JAMA. 1995;273(13):10221025.
  20. Levine RB, Lin F, Kern DE, Wright SM, Carrese J. Stories from early‐career women physicians who have left academic medicine: a qualitative study at a single institution. Acad Med. 2011;86(6):752758.
  21. Pololi LH, Civian JT, Brennan RT, Dottolo AL, Krupat E. Experiencing the culture of academic medicine: gender matters, a national study. J Gen Intern Med. 2013;28(2):201207.
  22. Yedidia MJ, Bickel J. Why aren't there more women leaders in academic medicine? tHe views of clinical department chairs. Acad Med. 2001;76(5):453465.
  23. Shin T. The gender gap in executive compensation: the role of female directors and chief executive officers. Ann Am Acad Pol Soc Sci. 2012(639):258278.
  24. Caniano DA, Sonnino RE, Paolo AM. Keys to career satisfaction: insights from a survey of women pediatric surgeons. J Pediatr Surg. 2004;39(6):984990.
  25. Sterne JA, White IR, Carlin JB, et al. Multiple imputation for missing data in epidemiological and clinical research: potential and pitfalls. BMJ. 2009;338:b2393.
  26. Imputation and Variance Estimation Software [computer program]. Ann Arbor, MI: Universtiy of Michigan; 2007.
  27. White IR, Royston P, Wood AM. Multiple Imputation using chained equations: issues and guidance for practice. Stat Med. 2010;30(4):377399.
  28. State of Hospital Medicine: 2010 Report Based on 2009 Data. Englewood, CO and Philadelphia, PA: Medical Group Management Association and Society of Hospital Medicine; 2010.
  29. Boulis AK, Jacobs JA. The Changing Face of Medicine: Women Doctors and the Evolution Of Health Care in America. Ithaca, NY: ILR Press/Cornell University Press; 2008.
  30. Babcock L, Laschever S. Women Don't Ask: Negotiation and the Gender Divide. Princeton, NJ: Princeton University Press; 2003.
  31. Sarfaty S, Kolb D, Barnett R, et al. Negotiation in academic medicine: a necessary career skill. J Womens Health (Larchmt). 2007;16(2):235244.
  32. Wade ME. Women and salary negotiation: the costs of self‐advocacy. Psychol Women Q. 2001;25:6576.
  33. State of Hospital Medicine: 2014 Report Based on 2013 Data. Englewood, CO and Philadelphia, PA: Medical Group Management Association and Society of Hospital Medicine; 2014.
  34. Isaac C, Lee B, Carnes M. Interventions that affect gender bias in hiring: a systematic review. Acad Med. 2009;84(10):14401446.
  35. Ley TJ, Hamilton BH. Sociology. The gender gap in NIH grant applications. Science. 2008;322(5907):14721474.
  36. Shollen SL, Bland CJ, Finstad DA, Taylor AL. Organizational climate and family life: how these factors affect the status of women faculty at one medical school. Acad Med. 2009;84(1):8794.
  37. Halperin TJ, Werler MM, Mulliken JB. Gender differences in the professional and private lives of plastic surgeons. Ann Plast Surg. 2010;64(6):775779.
  38. Wallace JE. Gender and supportive co‐worker relations in the medical profession. Gend Work Organ. 2014;21(1):117.
  39. Kaatz A, Carnes M. Stuck in the out‐group: Jennifer can't grow up, Jane's invisible, and Janet's over the hill. J Womens Health (Larchmt). 2014;23(6):481484.
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A matter of priorities? Exploring the persistent gender pay gap in hospital medicine
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Address for correspondence and reprint requests: A. Charlotta Weaver, MD, Assistant Professor of Medicine, Division of Hospital Medicine, 211 E. Ontario Street, Ste. 700, Chicago, IL 60611; Telephone: 312‐926‐2641; Fax: 312‐926‐6134; E‐mail: [email protected]
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Gender and Hospital Medicine

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We specialize in change leadership: A call for hospitalists to lead the quest for workforce gender equity

From a new concept to 44,000 practitioners in just 18 years,[1] there is no doubt that the word hospitalist is synonymous with innovation, leadership, growth, and change. Yet 2 articles in this month's Journal of Hospital Medicine prove that even our new field faces age‐old problems. Although women comprise half of all academic hospitalist and general internal medicine faculty, Burden et al.[2] showed that female hospitalists are less likely than male hospitalists to be division or section heads of hospital medicine, speakers at national meetings, and first or last authors on both research publications and editorials. This is made more concerning given that women are more likely to choose academic hospital medicine careers,[3] as they represent one‐third of all hospitalists but half of the academic hospitalist workforce.[2, 3] Findings in general internal medicine were similar, except that equal numbers of women and men were national meeting speakers and first authors on research publications (but not editorials). Weaver et al.[4] shed even more light on this disparity, and found that female hospitalists made $14,581 less per year than their male counterparts, even after adjusting for relevant differences. Weaver and colleagues also found other gender‐specific differences: women worked more nights and had fewer billable encounters per hospitalist shift than men.

Unfortunately, these trends are not new or limited to hospital medicine. For decades, almost equal numbers of women and men have entered medical school,[5] yet women are under‐represented in high status specialties,[6] less likely to be first or senior authors on original research studies compared to men,[7] less likely to be promoted,[8] and women physicians are consistently paid less than men across specialties.[9, 10] Simple analyses have not yet explained these disparities. Compared with men, women have similar leadership aspirations[11, 12] and are at least as effective as leaders.[13, 14, 15] Yet equity has not been attained.

Implicit bias research suggests that gender stereotypes influence women at all career stages.[16, 17, 18] For example, an elegant study conducted by Correll et al. identified a motherhood penalty, where indicating membership in the elementary school parent‐teacher organization on one's curriculum vitae hurt women's chances of employment and pay, but actually helped men.[19] Gender stereotypes exist, even among those who do not support their content. The universal reinforcement of such stereotypes over time leads to implicit but prescriptive rules about how women and men should act.[20] In particular, communal behaviors, including being cooperative, kind, and understanding, are typically associated with women, and agentic behaviors, including being ambitious and acting as a leader, are considered appropriate for men.[21] This leads to the think leader, think male phenomena, where we automatically associate men with leadership and higher status tasks (like first authorship or speaker invitations).[22, 23] Furthermore, acting against the stereotype (eg, a woman showing anger[24] or negotiating for more pay[25] or a man showing sadness[26]) can negatively impact wage and employment. Expecting social censure for violating gender norms, women develop a fear of the backlash that alone may shape behavior such that women may not express interest in having a high salary or negotiate for a raise.[27, 28, 29]

The specific system and institutional barriers that prevent female hospitalists from receiving equal pay and opportunities for leadership are not known, but one can surmise they are similar to those found in other specialties.[10, 30, 31] The findings of the studies of Burden et al.[2] and Weaver et al.[4] invite investigation of new questions specific to hospital medicine. Why are women in hospital medicine working more night shifts? Does this impact leadership or scholarship opportunities? Why are women documenting less productivity? Are they spending more time with patients, as they do in other settings?[32] What influences their practice choice? We would like to believe that there is something about hospital medicine that can explain the gender differences identified in these 2 studies. However, these data should prompt a serious and thorough examination of our specialty. We must accept that despite being a new specialty and a change leader, hospital medicine may not have escaped systematic gender bias that constrains the full participation and advancement of women.

But we believe that hospitalistsinnovators and change leaders in medicinewill be spurred to action to address the possibility of gender inequities. We do not need to know all of the causes to begin to address disparities, of every type, on an individual, institutional, and national level. As individuals, we can acknowledge that there are implicit assumptions that influence our decision making. No matter how unintentional, and even conflicting with evidence, these assumptions can lead us to judge women as less capable leaders than men or to automatically envision a high salary for a woman and man as different amounts. However, these automatic gender biases function as habits of mind, so they can be broken like any other unwanted habit.[33] Institutionally, we can also hold ourselves accountable for transparency in mentorship, leadership, scholarship, promotions, and wages to ensure diverse representation. We should routinely examine our practices to ensure the equitable hiring, pay, and promotion of our workforce.[18] National organizations and their respective journals should actively pursue diverse representation in leadership and membership on boards and committees, award nominees and recipients, and opportunities for invited editorials. Hospital medicinebeing young, innovative, and committed to changeis uniquely well suited to lead the charge for workforce equity. We can, and will, show the rest of medicine how it is done.

Disclosure

Nothing to report.

Files
References
  1. Society of Hospital Medicine. Milestones in the hospital medicine movement. Available at: http://www.hospitalmedicine.org/Web/About_SHM/Industry/shm_History.aspx. Accessed March 23, 2015.
  2. Burden M, Frank M, Keniston A, et al. Gender disparities in leadership and scholarly productivity of academic hospitalists. J Hosp Med. 2015;10(X):000000.
  3. Hinami K, Whelan C, Miller J, Wolosin R, Wetterneck T. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7:402410.
  4. Weaver C, Wetterneck T, Whelan C, Hinami K. A matter of priorities? Exploring the persistent gender pay gap in hospital medicine. J Hosp Med. 2015;10(8):486490.
  5. Association of American Medical Colleges. Table 1: medical students, selected years, 1965–2013. Available at: https://www.aamc.org/download/411782/data/2014_table1.pdf. Accessed March 23, 2015.
  6. Jagsi R, Griffith K, DeCastro R, Ubel P. Sex, role models, and specialty choices among graduates of US medical schools in 2006‐2008. J Am Coll Surg. 2014;218(3):345352.
  7. Jagsi R, Guancial E, Worobey C, et al. The “Gender Gap” in authorship of academic medical literature—a 35‐year perspective. N Engl J Med. 2006;355(3):281287.
  8. Nonnemaker L. Women physicians in academic medicine. N Engl J Med. 2000;342(6):399405.
  9. Jagsi R, Griffith K, Stewart A, Sambuco D, DeCastro R, Ubel P. Gender differences in the salaries of physician researchers. JAMA. 2012;307(22):24102417.
  10. Sasso A, Richards M, Chou C, Gerber S. The $16,819 pay gap for newly trained physicians: the unexplained trend of men earning more than women. Health Affairs. 2011;30(2):193201.
  11. Pololi L, Civian J, Brennan R, Dottalo A, Krupat E. Experiencing the culture of academic medicine: gender matters, a national study. J Gen Intern Med. 2013;28(2):201207.
  12. Wright A, Schwindt L, Bassford T, et al. Gender differences in academic advancement: patterns, causes, and potential solutions in one US College of Medicine. Acad Med. 2003;78(5):500508.
  13. Rosser V. Faculty and staff members perceptions of effective leadership: are there differences between men and women leaders? Equity Excell Educ. 2003;36(1):7181.
  14. Eagly A, Johannesen‐Schmidt M, Engen M. Transformational, transactional, and lasissez‐faire leadership styles: a meta‐analysis comparing women and men. Psychol Bull. 2003;129(4):569591.
  15. Isaac C, Griffin L, Carnes M. A qualitative study of faculty members' views of women chairs. J Womens Health (Larchmt). 2010;19(3):533546.
  16. Kaatz A, Carnes M. Stuck in the out‐group: Jennifer can't grow up, Jane's invisible, and Janet's over the hill. J Womens Health (Larchmt). 2014;23(6):481484.
  17. Eagly A, Carli L. Women and the labyrinth of leadership. Harv Bus Rev. 2007;85(9):6271.
  18. Isaac C, Lee B, Carnes M. Interventions that affect gender bias in hiring: a systematic review. Acad Med. 2009;84(10):14401446.
  19. Correll S, Benard S, Paik I. Getting a job: is there a motherhood penalty? Am J Sociol. 2017;112(5):12971339.
  20. Kolehmainen C, Brennan M, Filut A, Isaac C, Carnes M. Afraid of being “witchy with a ‘b’”: a qualitative study of how gender influences residents' experiences leading cardiopulmonary resuscitation. Acad Med. 2014;89(9):12761281.
  21. Bem S. The measurement of psychological androgyny. J Consult Clin Psychol. 1974;42:155162.
  22. Schein V, Mueller R, Lituchy T, Liu J. Think manager—think male: A global phenomenon? J Organ Behav. 1996;17(1):3341.
  23. Koenig A, Eagly A, Mitchell A, Ristikari T. Are leader stereotypes masculine? A meta‐analysis of three research paradigms. Psychol Bull. 2011;137(4):616642.
  24. Brescoll V, Uhlmann E. Can an angry woman get ahead? Status conferral, gender, and expression of emotion in the workplace. Psychol Sci. 2008;19(3):268275.
  25. Bowles H, Babcock L, Lai L. Social incentives for gender differences in the propensity to initiate negations: sometimes it does hurt to ask. Organ Behav Hum Decis Process 2007;103:84103.
  26. Tiedens L. Anger and advancement versus sadness and subjugation: the effect of negative emotion expressions on social status conferral. J Pers Soc Psychol. 2001;80(1):8694.
  27. Kray L, Thompson L, Galinsky A. Battle of the sexes: gender stereotype confirmation and reactance in negotiations. J Pers Soc Psychol. 2001;80(6):942958.
  28. Phelan J, Rudman L. Prejudice toward female leaders: Backlash effects and women's impression management dilemma. Soc Personal Psychol Compass. 2010;4(10):807820.
  29. Carnes M. Commentary: deconstructing gender difference. Acad Med. 2010;85(4):575577.
  30. Shollen S, Bland C, Finstad D, Taylor A. Organizational climate and family life: how these factors affect the status of women faculty at one medical school. Acad Med. 2009;84(1):8794.
  31. Poppas A, Cummings J, Dorbala S, Douglas P, Foster E, Limacher M. Survey results: a decade of change in professional life in cardiology: a 2008 report of the ACC women in cardiology council. J Am Coll Cardiol. 2008;52(25):22152226.
  32. Jefferson L, Bloor K, Birks Y, Hewitt C, Bland M. Effect of physicians' gender on communication and consultation length: a systematic review and meta‐analysis. J Health Serv Res Policy. 2013;18:242248.
  33. Carnes M, Devine P, Baier Manwell L, et al. The effect of an intervention to break the gender bias habit for faculty at one institution: a cluster randomized, controlled trial. Acad Med. 2015;90(2):221230.
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From a new concept to 44,000 practitioners in just 18 years,[1] there is no doubt that the word hospitalist is synonymous with innovation, leadership, growth, and change. Yet 2 articles in this month's Journal of Hospital Medicine prove that even our new field faces age‐old problems. Although women comprise half of all academic hospitalist and general internal medicine faculty, Burden et al.[2] showed that female hospitalists are less likely than male hospitalists to be division or section heads of hospital medicine, speakers at national meetings, and first or last authors on both research publications and editorials. This is made more concerning given that women are more likely to choose academic hospital medicine careers,[3] as they represent one‐third of all hospitalists but half of the academic hospitalist workforce.[2, 3] Findings in general internal medicine were similar, except that equal numbers of women and men were national meeting speakers and first authors on research publications (but not editorials). Weaver et al.[4] shed even more light on this disparity, and found that female hospitalists made $14,581 less per year than their male counterparts, even after adjusting for relevant differences. Weaver and colleagues also found other gender‐specific differences: women worked more nights and had fewer billable encounters per hospitalist shift than men.

Unfortunately, these trends are not new or limited to hospital medicine. For decades, almost equal numbers of women and men have entered medical school,[5] yet women are under‐represented in high status specialties,[6] less likely to be first or senior authors on original research studies compared to men,[7] less likely to be promoted,[8] and women physicians are consistently paid less than men across specialties.[9, 10] Simple analyses have not yet explained these disparities. Compared with men, women have similar leadership aspirations[11, 12] and are at least as effective as leaders.[13, 14, 15] Yet equity has not been attained.

Implicit bias research suggests that gender stereotypes influence women at all career stages.[16, 17, 18] For example, an elegant study conducted by Correll et al. identified a motherhood penalty, where indicating membership in the elementary school parent‐teacher organization on one's curriculum vitae hurt women's chances of employment and pay, but actually helped men.[19] Gender stereotypes exist, even among those who do not support their content. The universal reinforcement of such stereotypes over time leads to implicit but prescriptive rules about how women and men should act.[20] In particular, communal behaviors, including being cooperative, kind, and understanding, are typically associated with women, and agentic behaviors, including being ambitious and acting as a leader, are considered appropriate for men.[21] This leads to the think leader, think male phenomena, where we automatically associate men with leadership and higher status tasks (like first authorship or speaker invitations).[22, 23] Furthermore, acting against the stereotype (eg, a woman showing anger[24] or negotiating for more pay[25] or a man showing sadness[26]) can negatively impact wage and employment. Expecting social censure for violating gender norms, women develop a fear of the backlash that alone may shape behavior such that women may not express interest in having a high salary or negotiate for a raise.[27, 28, 29]

The specific system and institutional barriers that prevent female hospitalists from receiving equal pay and opportunities for leadership are not known, but one can surmise they are similar to those found in other specialties.[10, 30, 31] The findings of the studies of Burden et al.[2] and Weaver et al.[4] invite investigation of new questions specific to hospital medicine. Why are women in hospital medicine working more night shifts? Does this impact leadership or scholarship opportunities? Why are women documenting less productivity? Are they spending more time with patients, as they do in other settings?[32] What influences their practice choice? We would like to believe that there is something about hospital medicine that can explain the gender differences identified in these 2 studies. However, these data should prompt a serious and thorough examination of our specialty. We must accept that despite being a new specialty and a change leader, hospital medicine may not have escaped systematic gender bias that constrains the full participation and advancement of women.

But we believe that hospitalistsinnovators and change leaders in medicinewill be spurred to action to address the possibility of gender inequities. We do not need to know all of the causes to begin to address disparities, of every type, on an individual, institutional, and national level. As individuals, we can acknowledge that there are implicit assumptions that influence our decision making. No matter how unintentional, and even conflicting with evidence, these assumptions can lead us to judge women as less capable leaders than men or to automatically envision a high salary for a woman and man as different amounts. However, these automatic gender biases function as habits of mind, so they can be broken like any other unwanted habit.[33] Institutionally, we can also hold ourselves accountable for transparency in mentorship, leadership, scholarship, promotions, and wages to ensure diverse representation. We should routinely examine our practices to ensure the equitable hiring, pay, and promotion of our workforce.[18] National organizations and their respective journals should actively pursue diverse representation in leadership and membership on boards and committees, award nominees and recipients, and opportunities for invited editorials. Hospital medicinebeing young, innovative, and committed to changeis uniquely well suited to lead the charge for workforce equity. We can, and will, show the rest of medicine how it is done.

Disclosure

Nothing to report.

From a new concept to 44,000 practitioners in just 18 years,[1] there is no doubt that the word hospitalist is synonymous with innovation, leadership, growth, and change. Yet 2 articles in this month's Journal of Hospital Medicine prove that even our new field faces age‐old problems. Although women comprise half of all academic hospitalist and general internal medicine faculty, Burden et al.[2] showed that female hospitalists are less likely than male hospitalists to be division or section heads of hospital medicine, speakers at national meetings, and first or last authors on both research publications and editorials. This is made more concerning given that women are more likely to choose academic hospital medicine careers,[3] as they represent one‐third of all hospitalists but half of the academic hospitalist workforce.[2, 3] Findings in general internal medicine were similar, except that equal numbers of women and men were national meeting speakers and first authors on research publications (but not editorials). Weaver et al.[4] shed even more light on this disparity, and found that female hospitalists made $14,581 less per year than their male counterparts, even after adjusting for relevant differences. Weaver and colleagues also found other gender‐specific differences: women worked more nights and had fewer billable encounters per hospitalist shift than men.

Unfortunately, these trends are not new or limited to hospital medicine. For decades, almost equal numbers of women and men have entered medical school,[5] yet women are under‐represented in high status specialties,[6] less likely to be first or senior authors on original research studies compared to men,[7] less likely to be promoted,[8] and women physicians are consistently paid less than men across specialties.[9, 10] Simple analyses have not yet explained these disparities. Compared with men, women have similar leadership aspirations[11, 12] and are at least as effective as leaders.[13, 14, 15] Yet equity has not been attained.

Implicit bias research suggests that gender stereotypes influence women at all career stages.[16, 17, 18] For example, an elegant study conducted by Correll et al. identified a motherhood penalty, where indicating membership in the elementary school parent‐teacher organization on one's curriculum vitae hurt women's chances of employment and pay, but actually helped men.[19] Gender stereotypes exist, even among those who do not support their content. The universal reinforcement of such stereotypes over time leads to implicit but prescriptive rules about how women and men should act.[20] In particular, communal behaviors, including being cooperative, kind, and understanding, are typically associated with women, and agentic behaviors, including being ambitious and acting as a leader, are considered appropriate for men.[21] This leads to the think leader, think male phenomena, where we automatically associate men with leadership and higher status tasks (like first authorship or speaker invitations).[22, 23] Furthermore, acting against the stereotype (eg, a woman showing anger[24] or negotiating for more pay[25] or a man showing sadness[26]) can negatively impact wage and employment. Expecting social censure for violating gender norms, women develop a fear of the backlash that alone may shape behavior such that women may not express interest in having a high salary or negotiate for a raise.[27, 28, 29]

The specific system and institutional barriers that prevent female hospitalists from receiving equal pay and opportunities for leadership are not known, but one can surmise they are similar to those found in other specialties.[10, 30, 31] The findings of the studies of Burden et al.[2] and Weaver et al.[4] invite investigation of new questions specific to hospital medicine. Why are women in hospital medicine working more night shifts? Does this impact leadership or scholarship opportunities? Why are women documenting less productivity? Are they spending more time with patients, as they do in other settings?[32] What influences their practice choice? We would like to believe that there is something about hospital medicine that can explain the gender differences identified in these 2 studies. However, these data should prompt a serious and thorough examination of our specialty. We must accept that despite being a new specialty and a change leader, hospital medicine may not have escaped systematic gender bias that constrains the full participation and advancement of women.

But we believe that hospitalistsinnovators and change leaders in medicinewill be spurred to action to address the possibility of gender inequities. We do not need to know all of the causes to begin to address disparities, of every type, on an individual, institutional, and national level. As individuals, we can acknowledge that there are implicit assumptions that influence our decision making. No matter how unintentional, and even conflicting with evidence, these assumptions can lead us to judge women as less capable leaders than men or to automatically envision a high salary for a woman and man as different amounts. However, these automatic gender biases function as habits of mind, so they can be broken like any other unwanted habit.[33] Institutionally, we can also hold ourselves accountable for transparency in mentorship, leadership, scholarship, promotions, and wages to ensure diverse representation. We should routinely examine our practices to ensure the equitable hiring, pay, and promotion of our workforce.[18] National organizations and their respective journals should actively pursue diverse representation in leadership and membership on boards and committees, award nominees and recipients, and opportunities for invited editorials. Hospital medicinebeing young, innovative, and committed to changeis uniquely well suited to lead the charge for workforce equity. We can, and will, show the rest of medicine how it is done.

Disclosure

Nothing to report.

References
  1. Society of Hospital Medicine. Milestones in the hospital medicine movement. Available at: http://www.hospitalmedicine.org/Web/About_SHM/Industry/shm_History.aspx. Accessed March 23, 2015.
  2. Burden M, Frank M, Keniston A, et al. Gender disparities in leadership and scholarly productivity of academic hospitalists. J Hosp Med. 2015;10(X):000000.
  3. Hinami K, Whelan C, Miller J, Wolosin R, Wetterneck T. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7:402410.
  4. Weaver C, Wetterneck T, Whelan C, Hinami K. A matter of priorities? Exploring the persistent gender pay gap in hospital medicine. J Hosp Med. 2015;10(8):486490.
  5. Association of American Medical Colleges. Table 1: medical students, selected years, 1965–2013. Available at: https://www.aamc.org/download/411782/data/2014_table1.pdf. Accessed March 23, 2015.
  6. Jagsi R, Griffith K, DeCastro R, Ubel P. Sex, role models, and specialty choices among graduates of US medical schools in 2006‐2008. J Am Coll Surg. 2014;218(3):345352.
  7. Jagsi R, Guancial E, Worobey C, et al. The “Gender Gap” in authorship of academic medical literature—a 35‐year perspective. N Engl J Med. 2006;355(3):281287.
  8. Nonnemaker L. Women physicians in academic medicine. N Engl J Med. 2000;342(6):399405.
  9. Jagsi R, Griffith K, Stewart A, Sambuco D, DeCastro R, Ubel P. Gender differences in the salaries of physician researchers. JAMA. 2012;307(22):24102417.
  10. Sasso A, Richards M, Chou C, Gerber S. The $16,819 pay gap for newly trained physicians: the unexplained trend of men earning more than women. Health Affairs. 2011;30(2):193201.
  11. Pololi L, Civian J, Brennan R, Dottalo A, Krupat E. Experiencing the culture of academic medicine: gender matters, a national study. J Gen Intern Med. 2013;28(2):201207.
  12. Wright A, Schwindt L, Bassford T, et al. Gender differences in academic advancement: patterns, causes, and potential solutions in one US College of Medicine. Acad Med. 2003;78(5):500508.
  13. Rosser V. Faculty and staff members perceptions of effective leadership: are there differences between men and women leaders? Equity Excell Educ. 2003;36(1):7181.
  14. Eagly A, Johannesen‐Schmidt M, Engen M. Transformational, transactional, and lasissez‐faire leadership styles: a meta‐analysis comparing women and men. Psychol Bull. 2003;129(4):569591.
  15. Isaac C, Griffin L, Carnes M. A qualitative study of faculty members' views of women chairs. J Womens Health (Larchmt). 2010;19(3):533546.
  16. Kaatz A, Carnes M. Stuck in the out‐group: Jennifer can't grow up, Jane's invisible, and Janet's over the hill. J Womens Health (Larchmt). 2014;23(6):481484.
  17. Eagly A, Carli L. Women and the labyrinth of leadership. Harv Bus Rev. 2007;85(9):6271.
  18. Isaac C, Lee B, Carnes M. Interventions that affect gender bias in hiring: a systematic review. Acad Med. 2009;84(10):14401446.
  19. Correll S, Benard S, Paik I. Getting a job: is there a motherhood penalty? Am J Sociol. 2017;112(5):12971339.
  20. Kolehmainen C, Brennan M, Filut A, Isaac C, Carnes M. Afraid of being “witchy with a ‘b’”: a qualitative study of how gender influences residents' experiences leading cardiopulmonary resuscitation. Acad Med. 2014;89(9):12761281.
  21. Bem S. The measurement of psychological androgyny. J Consult Clin Psychol. 1974;42:155162.
  22. Schein V, Mueller R, Lituchy T, Liu J. Think manager—think male: A global phenomenon? J Organ Behav. 1996;17(1):3341.
  23. Koenig A, Eagly A, Mitchell A, Ristikari T. Are leader stereotypes masculine? A meta‐analysis of three research paradigms. Psychol Bull. 2011;137(4):616642.
  24. Brescoll V, Uhlmann E. Can an angry woman get ahead? Status conferral, gender, and expression of emotion in the workplace. Psychol Sci. 2008;19(3):268275.
  25. Bowles H, Babcock L, Lai L. Social incentives for gender differences in the propensity to initiate negations: sometimes it does hurt to ask. Organ Behav Hum Decis Process 2007;103:84103.
  26. Tiedens L. Anger and advancement versus sadness and subjugation: the effect of negative emotion expressions on social status conferral. J Pers Soc Psychol. 2001;80(1):8694.
  27. Kray L, Thompson L, Galinsky A. Battle of the sexes: gender stereotype confirmation and reactance in negotiations. J Pers Soc Psychol. 2001;80(6):942958.
  28. Phelan J, Rudman L. Prejudice toward female leaders: Backlash effects and women's impression management dilemma. Soc Personal Psychol Compass. 2010;4(10):807820.
  29. Carnes M. Commentary: deconstructing gender difference. Acad Med. 2010;85(4):575577.
  30. Shollen S, Bland C, Finstad D, Taylor A. Organizational climate and family life: how these factors affect the status of women faculty at one medical school. Acad Med. 2009;84(1):8794.
  31. Poppas A, Cummings J, Dorbala S, Douglas P, Foster E, Limacher M. Survey results: a decade of change in professional life in cardiology: a 2008 report of the ACC women in cardiology council. J Am Coll Cardiol. 2008;52(25):22152226.
  32. Jefferson L, Bloor K, Birks Y, Hewitt C, Bland M. Effect of physicians' gender on communication and consultation length: a systematic review and meta‐analysis. J Health Serv Res Policy. 2013;18:242248.
  33. Carnes M, Devine P, Baier Manwell L, et al. The effect of an intervention to break the gender bias habit for faculty at one institution: a cluster randomized, controlled trial. Acad Med. 2015;90(2):221230.
References
  1. Society of Hospital Medicine. Milestones in the hospital medicine movement. Available at: http://www.hospitalmedicine.org/Web/About_SHM/Industry/shm_History.aspx. Accessed March 23, 2015.
  2. Burden M, Frank M, Keniston A, et al. Gender disparities in leadership and scholarly productivity of academic hospitalists. J Hosp Med. 2015;10(X):000000.
  3. Hinami K, Whelan C, Miller J, Wolosin R, Wetterneck T. Job characteristics, satisfaction, and burnout across hospitalist practice models. J Hosp Med. 2012;7:402410.
  4. Weaver C, Wetterneck T, Whelan C, Hinami K. A matter of priorities? Exploring the persistent gender pay gap in hospital medicine. J Hosp Med. 2015;10(8):486490.
  5. Association of American Medical Colleges. Table 1: medical students, selected years, 1965–2013. Available at: https://www.aamc.org/download/411782/data/2014_table1.pdf. Accessed March 23, 2015.
  6. Jagsi R, Griffith K, DeCastro R, Ubel P. Sex, role models, and specialty choices among graduates of US medical schools in 2006‐2008. J Am Coll Surg. 2014;218(3):345352.
  7. Jagsi R, Guancial E, Worobey C, et al. The “Gender Gap” in authorship of academic medical literature—a 35‐year perspective. N Engl J Med. 2006;355(3):281287.
  8. Nonnemaker L. Women physicians in academic medicine. N Engl J Med. 2000;342(6):399405.
  9. Jagsi R, Griffith K, Stewart A, Sambuco D, DeCastro R, Ubel P. Gender differences in the salaries of physician researchers. JAMA. 2012;307(22):24102417.
  10. Sasso A, Richards M, Chou C, Gerber S. The $16,819 pay gap for newly trained physicians: the unexplained trend of men earning more than women. Health Affairs. 2011;30(2):193201.
  11. Pololi L, Civian J, Brennan R, Dottalo A, Krupat E. Experiencing the culture of academic medicine: gender matters, a national study. J Gen Intern Med. 2013;28(2):201207.
  12. Wright A, Schwindt L, Bassford T, et al. Gender differences in academic advancement: patterns, causes, and potential solutions in one US College of Medicine. Acad Med. 2003;78(5):500508.
  13. Rosser V. Faculty and staff members perceptions of effective leadership: are there differences between men and women leaders? Equity Excell Educ. 2003;36(1):7181.
  14. Eagly A, Johannesen‐Schmidt M, Engen M. Transformational, transactional, and lasissez‐faire leadership styles: a meta‐analysis comparing women and men. Psychol Bull. 2003;129(4):569591.
  15. Isaac C, Griffin L, Carnes M. A qualitative study of faculty members' views of women chairs. J Womens Health (Larchmt). 2010;19(3):533546.
  16. Kaatz A, Carnes M. Stuck in the out‐group: Jennifer can't grow up, Jane's invisible, and Janet's over the hill. J Womens Health (Larchmt). 2014;23(6):481484.
  17. Eagly A, Carli L. Women and the labyrinth of leadership. Harv Bus Rev. 2007;85(9):6271.
  18. Isaac C, Lee B, Carnes M. Interventions that affect gender bias in hiring: a systematic review. Acad Med. 2009;84(10):14401446.
  19. Correll S, Benard S, Paik I. Getting a job: is there a motherhood penalty? Am J Sociol. 2017;112(5):12971339.
  20. Kolehmainen C, Brennan M, Filut A, Isaac C, Carnes M. Afraid of being “witchy with a ‘b’”: a qualitative study of how gender influences residents' experiences leading cardiopulmonary resuscitation. Acad Med. 2014;89(9):12761281.
  21. Bem S. The measurement of psychological androgyny. J Consult Clin Psychol. 1974;42:155162.
  22. Schein V, Mueller R, Lituchy T, Liu J. Think manager—think male: A global phenomenon? J Organ Behav. 1996;17(1):3341.
  23. Koenig A, Eagly A, Mitchell A, Ristikari T. Are leader stereotypes masculine? A meta‐analysis of three research paradigms. Psychol Bull. 2011;137(4):616642.
  24. Brescoll V, Uhlmann E. Can an angry woman get ahead? Status conferral, gender, and expression of emotion in the workplace. Psychol Sci. 2008;19(3):268275.
  25. Bowles H, Babcock L, Lai L. Social incentives for gender differences in the propensity to initiate negations: sometimes it does hurt to ask. Organ Behav Hum Decis Process 2007;103:84103.
  26. Tiedens L. Anger and advancement versus sadness and subjugation: the effect of negative emotion expressions on social status conferral. J Pers Soc Psychol. 2001;80(1):8694.
  27. Kray L, Thompson L, Galinsky A. Battle of the sexes: gender stereotype confirmation and reactance in negotiations. J Pers Soc Psychol. 2001;80(6):942958.
  28. Phelan J, Rudman L. Prejudice toward female leaders: Backlash effects and women's impression management dilemma. Soc Personal Psychol Compass. 2010;4(10):807820.
  29. Carnes M. Commentary: deconstructing gender difference. Acad Med. 2010;85(4):575577.
  30. Shollen S, Bland C, Finstad D, Taylor A. Organizational climate and family life: how these factors affect the status of women faculty at one medical school. Acad Med. 2009;84(1):8794.
  31. Poppas A, Cummings J, Dorbala S, Douglas P, Foster E, Limacher M. Survey results: a decade of change in professional life in cardiology: a 2008 report of the ACC women in cardiology council. J Am Coll Cardiol. 2008;52(25):22152226.
  32. Jefferson L, Bloor K, Birks Y, Hewitt C, Bland M. Effect of physicians' gender on communication and consultation length: a systematic review and meta‐analysis. J Health Serv Res Policy. 2013;18:242248.
  33. Carnes M, Devine P, Baier Manwell L, et al. The effect of an intervention to break the gender bias habit for faculty at one institution: a cluster randomized, controlled trial. Acad Med. 2015;90(2):221230.
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We specialize in change leadership: A call for hospitalists to lead the quest for workforce gender equity
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Address for correspondence and reprint requests: Ann M. Sheehy, MD, Department of Medicine, Division of Hospital Medicine, University of Wisconsin School of Medicine and Public Health, 1685 Highland Ave, MFCB 3126, Madison, Wisconsin 53705; Telephone: 608‐262‐2434; Fax: 608‐265‐1420; E‐mail: [email protected]
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Discharge Before Noon

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Discharge before noon: Effect on throughput and sustainability

It is thought that late afternoon hospital discharges create admission bottlenecks in the emergency department (ED).[1] As hospital occupancy increases, so too does ED boarding time.[2] Increased ED boarding time can result in increased length of stay (LOS)[3] and reduced patient and staff satisfaction.[4] Early in the day discharge programs are intended to improve hospital throughput.[5, 6, 7, 8, 9] Yet, ED admission timing is, in part, determined by external fluctuations in ED volume and acuity that early discharges do not impact.[10] We previously reported that high levels of discharge before noon (DBN) from inpatient medicine units is achievable through a multidisciplinary intervention.[5] We now evaluate the effect of this intervention upon admission patterns and the sustainability of the DBN initiative.

The DBN intervention consisted of afternoon interdisciplinary rounds, a checklist of team members' responsibilities, a standardized electronic communication tool, and daily feedback on the DBN rate.[5] The intervention resulted in an increase in the DBN rate from 11% to 38% in the first 13 months. We previously reported effects upon the discharged patient as measured by the observed to expected length of stay (O:E LOS) and 30‐day readmission rate. We now assess the effect of our DBN initiative on the subsequent patient and hospital throughput. Our objectives for this study were: (1) to determine the effect of DBN on the admission arrival times and admissions per hour to the units, and (2) in a separate data collection and analysis, to determine if the increased DBN rate is sustainable. We hypothesize that DBN results in admissions arriving onto the units earlier in the day. We further hypothesize that because of this redistribution, DBN will level the load of admissions, reducing admissions per hour peaks that can occur late in the day.

METHODS

Study Design, Participants, and Setting

This is a pre‐/postretrospective analysis evaluating the effect of a previously described DBN intervention.[5] Two inpatient acute‐care medicine units at NYU Langone Medical Center's Tisch Hospital, a 725‐bed, urban, academic medical center, were included in the analysis. All patients admitted to the units underwent the intervention.

Intervention

The DBN intervention began with a multidisciplinary kickoff event in which all team members received education on the importance of DBN, a clear description of roles in the DBN process, and a corresponding checklist of responsibilities. The checklist was utilized at new afternoon interdisciplinary rounds intended to identify next‐day DBNs. Patients identified in afternoon interdisciplinary rounds were logged in a DBN website that generated twice‐daily automated emails to communicate the planned DBN list to frontline staff and key stakeholders. Daily, real‐time feedback on the DBN rate was provided to floor staff.

Measures

Admission Arrival Time

The arrival location and time to any hospital area (ED, radiology, inpatient medical unit) is recorded in the electronic medical record (Epic, Madison, WI) at the time the patient arrives by the patient unit assistant or unit clerk. We obtained the arrival time to each hospital unit throughout the patient's hospitalization for all patients arriving to the study units during their hospitalization between June 1, 2011 and March 4, 2012 (the baseline period) and March 5, 2012 and June 31, 2013 (the intervention period). Data from October 25, 2012 to the end of January 2013 were excluded due to hospital closure from Hurricane Sandy. These time periods and exclusions match those used in our previous DBN article.[5] To match that study's criteria, we excluded patients on the units in the patient class observation, inpatient hospice, and those patients whose discharge disposition was expired or hospice.

ED Admissions

All patients with a first inpatient unit location of ED and no other inpatient unit location prior to arrival on the study units were included in the ED admission analysis. Units that treat but do not provide long‐term boarding/housing of inpatientssuch as radiology, hemodialysis, and cardiac catheterizationwere not considered in determining ED admission status. Even if a patient had recorded arrival to those areas between ED and study unit arrival, these patients were considered ED admissions, as they were never admitted to another inpatient unit.

Transfers and Direct Admissions

All patients whose first inpatient unit location was the study units were included in the transfers and direct admissions analysis. Those patients who were recorded as coming from another inpatient unit (such as another medical, surgical, step‐down, intensive care, or other specialty unit) prior to study unit arrival were included as intrahospital transfers.

Level Load of Admissions

Level loading is a lean methodology term that describes reducing the unevenness in a production line to enhance efficiency.[11] We evaluated this by comparing the admissions per hour (density distribution) to the studied units in the pre‐ and postintervention periods.

Sustainability of the DBN Intervention

The DBN intervention, as described in our original article, continues uninterrupted. Using the same methodology, inclusion criteria, exclusion criteria, and data analysis previously described, we gathered the discharge date and time as recorded by the patient unit assistant for all patients discharged from the study units for the 18 months (July 1, 2013 to December 31, 2014) after our original article to evaluate the sustainability of our improvement in DBN rates.

Statistical Analysis

Median admission time to the floor was compared between the 2 time periods using the Wilcoxon rank sum test. This is a non parametric test of the null hypothesis that the two time periods have the same distributions of admission time to the floor. To evaluate statistical significance, each admission time is arranged in order of magnitude and assigned a rank. The sum of the ranks for each group is calculated and the smaller rank sum (the W statistic) is compared to an expected range of values based on the sample sizes. If this value is out of range then one can reject the null hypothesis. The density distributions of admissions during the 2 time periods were compared using the Kolmogorov‐Smirnov test. The 2‐sided Kolmogorov‐Smirnov test evaluates the maximum distance (D) between the distributions of 2 samples.[12] We chose this test because it evaluates differences between both the position and shape of the distributions of the samples.

RESULTS

Setting Characteristics

The units had an average occupancy rate of 86.8% for the duration of the study. The average number of total discharges per day was 9.8. The average absolute length of stay was 5.6 days.

Admission Arrival Time to the Unit

ED Admissions

A total of 6566 patients were admitted from the ED to the units, 2756 in the baseline period and 3810 in the intervention period. The median arrival time to the units of ED admissions grouped by hour of the day moved by 1 hour, from 5 pm to 4 pm from the baseline to intervention period, and this change was statistically significant (W=16,211,778, P<0.01) (Figure 1).

Figure 1
Timing of admissions from the emergency department by hour of the day. Count = number of patients.

Transfers and Direct Admissions

A total of 823 patients were transferred or directly admitted to the units, 310 in the baseline period and 513 in the intervention period. The median arrival time to the units grouped by hour of the day moved 1 hour from 5 pm to 4 pm, and this change was statistically significant (W=324,532, P<0.01) (Figure 2).

Figure 2
Timing of transfers and direct admissions by hour of the day. Count = number of patients.

Level Load of Admissions

In the baseline period, the highest density of ED admissions occurred during the 5‐hour period from 5 pm to 10 pm, when 42.3% of daily admissions arrived (Figure 3). In the intervention period, the highest density of admissions occurred during the 5‐hour period from 3 pm to 8 pm, when 40.0% of daily admissions arrived. The difference between the density distributions for the 2 time periods was found to be statistically significant using the Kolmogorov‐Smirnov test (D=0.03, P<0.01).

Figure 3
Density of emergency department (ED) admissions and transfers by hour of the day. Density = number of admissions per hour.

In the baseline period, the highest density of transfers and direct admissions occurred during the 5‐hour period from 3 pm to 8 pm, when 51.7% of daily admissions arrived (Figure 3). In the intervention time period, the highest density of transfers and direct admissions occurred during the 5‐hour time period from 2 pm to 7 pm, when 50.3% of daily admissions arrived. The difference between the density distributions of transfers and direct admissions for the 2 time periods was not statistically significant using the Kolmogorov‐Smirnov test (D=0.04, P=0.3).

Sustainability of the DBN Intervention

For the 18 months after the prior reported DBN intervention period, an additional 5505 total discharges were included for analysis. Of these, 1796 were DBN. The average DBN rate for the study units from March 5, 2012 until December 31, 2014 (the original intervention period plus the additional 18 months of new data) is 35% (Figure 4).

Figure 4
Calendar month percent discharge before noon (DBN).

DISCUSSION

The potential effects of DBN are multiple. By reducing the O:E LOS and allowing patients the time to acquire their medications, make follow‐up appointments, and ask questions while providers are still in the hospital, our DBN initiative impacts the discharged patient's quality, safety, and efficiency of care.[5] We now report how the DBN initiative potentially impacts the subsequent patient's efficiency of care and hospital throughput. In addition, we show that the DBN initiative is sustainable over years.

Over the same time course as our initial DBN intervention, we found a statistically significant change in the time when admitted patients arrive on the floor. This was true of those patients admitted through the ED and those directly admitted to the floor. In a complex hospital system with many factors both internal (bed cleaning, patient transportation) and external (natural variations in ED volume and acuity) affecting the timing of admissions, it is important to note that increasing the DBN rate correlates with a change in median admission arrival time. From a patient safety standpoint, any initiative that moves admissions away from evening and night hours and takes advantage of (usually more robust) day staffing is a potentially favorable intervention.[13]

We observed a statistically significant reduction of highest frequency peaks of ED admissions. It appears that opening beds up earlier in the day through DBN may help level the load of admissions from the ED. There was no effect on highest frequency peaks of transfer admissions to the floor. This may be due to the timing of transfers being dependent on factors other than bed availability, such as timing of transportation to the hospital or the timing of planned treatment.

We also found that the DBN intervention has created sustainable increases in the DBN rate. Since our initial publication, we have received direct communication from physicians, administrators and managers in 6 different states and 2 foreign countries asking for additional information or reporting that their hospitals are pursuing similar goals. Some of the most common questions asked include: Are your results sustained? and What do you think is a reasonable DBN goal? We have attempted to answer both of these questions. We previously reported improvement to an average DBN rate of 38% over the first 13 intervention months. With more time, we now see an absolute DBN rate of 35%. In November 2014, we restructured our medicine service to become geographic, so that the same group of doctors, trainees, nurses, care managers, and social workers care for patients on a single ward. Since this initiative, our DBN rate has climbed to greater than 40%. We hope to report further on this new intervention in the future. Similar hospital centers can consider using our experience on an inpatient acute‐care medical unit in an urban environment as a benchmark for setting hospital metric goals for early‐in‐the‐day discharge.

Several studies have previously reported on early‐in‐the‐day discharge initiatives. These were smaller studies that focused on descriptions of the type of intervention, including a discharge brunch on an obstetrics floor,[8] scheduled discharges,[6] in‐room displays of expected day and time of discharge,[9] and a physician‐centered discharge process.[7] Our study is substantially larger, focused on inpatient medicine units, and reports the effect of significant changes in DBN on patient and hospital metrics.

Our study had several limitations. The study is based in a single site, potentially limiting the generalizability of our findings. The hospital underwent tremendous change during the course of the intervention, including its temporary closure due to Hurricane Sandy. We cannot exclude effects related to shifts in volume and possible differences in the pre‐ and post‐time period patient populations. The prior study evaluated the population of discharged patients, but the admission analysis in this study involves the population of admitted patients. There may be slight differences in the populations due to the inclusion of patients who were admitted but not discharged from the units (for instance due to transfer after admission). Though the findings on admission arrival time correlate well with the increasing DBN rates, as they occur during the same time and in the same direction (earlier in the day), we are unable to conclude if the effect is causative. There were many interventions ongoing throughout the hospital to improve throughput, and these programs could have created local trends that confound our data. We are also unable to evaluate the clinical significance of a 1‐hour shift in median admission arrival time. Each hospital system must determine for itself if the time and resource investment in DBN is worth the change in admission timing described. We completed this analysis with the perspective of the inpatient medical unit experience, including the timing and number of admissions arriving to the units. We cannot exclude the possibility that changes in arrival times or boarding trends in the ED contribute to our findings.

CONCLUSION

In our hospital, a successful DBN initiative correlates with movement of ED admissions and transfers onto the inpatient units earlier in the day. There was a leveling of the load for ED admissions over the same time period. DBN continues to be an achievable hospital goal, and we provide a potential benchmark for similar hospitals.

Disclosure

Nothing to report.

Files
References
  1. Khanna S, Boyle J, Good N, Lind J. Impact of admission and discharge peak times on hospital overcrowding. Stud Health Technol Inform. 2011;168:8288.
  2. Rathlev NK, Obendorfer D, White LF, et al. Time series analysis of emergency department length of stay per 8‐hour shift. West J Emerg Med. 2012;13(2):163168.
  3. White BA, Biddinger PD, Chang Y, Grabowski B, Carignan S, Brown DF. Boarding inpatients in the emergency department increases discharged patient length of stay. J Emerg Med. 2013;44(1):230235.
  4. Derlet RW, Richards JR. Overcrowding in the nation's emergency departments: complex causes and disturbing effects. Ann Emerg Med. 2000;35(1):6368.
  5. Wertheimer B, Jacobs RE, Bailey M, et al. Discharge before noon: an achievable hospital goal. J Hosp Med. 2014;9(4):210214.
  6. Bergstrom J FL, Quinn M, Wheeler H. All roads lead to scheduled discharges. Nursing. 2008;38(12):6163.
  7. Kravet SJ, Levine RB, Rubin HR, Wright SM. Discharging patients earlier in the day: a concept worth evaluating. Health Care Manag (Frederick). 2007;26(2):142146.
  8. Lucia MA, Mullaly LM. The discharge brunch: reducing chaos and increasing smiles on the OB unit. Nurs Womens Health. 2009;13(5):402409.
  9. Manning DM, Tammel KJ, Blegen RN, et al. In‐room display of day and time patient is anticipated to leave hospital: a “discharge appointment”. J Hosp Med. 2007;2(1):1316.
  10. Arkun A, Briggs WM, Patel S, Datillo PA, Bove J, Birkhahn RH. Emergency department crowding: factors influencing flow. West J Emerg Med. 2010;11(1):1015.
  11. Liker JK. The Toyota Way: 14 Management Principles From the World's Greatest Manufacturer. New York, NY: McGraw‐Hill; 2004.
  12. Thas O. Comparing Distributions. New York, NY: Springer; 2010.
  13. Peberdy MA, Ornato JP, Larkin GL, et al. Survival from in‐hospital cardiac arrest during nights and weekends. JAMA. 2008;299(7):785792.
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It is thought that late afternoon hospital discharges create admission bottlenecks in the emergency department (ED).[1] As hospital occupancy increases, so too does ED boarding time.[2] Increased ED boarding time can result in increased length of stay (LOS)[3] and reduced patient and staff satisfaction.[4] Early in the day discharge programs are intended to improve hospital throughput.[5, 6, 7, 8, 9] Yet, ED admission timing is, in part, determined by external fluctuations in ED volume and acuity that early discharges do not impact.[10] We previously reported that high levels of discharge before noon (DBN) from inpatient medicine units is achievable through a multidisciplinary intervention.[5] We now evaluate the effect of this intervention upon admission patterns and the sustainability of the DBN initiative.

The DBN intervention consisted of afternoon interdisciplinary rounds, a checklist of team members' responsibilities, a standardized electronic communication tool, and daily feedback on the DBN rate.[5] The intervention resulted in an increase in the DBN rate from 11% to 38% in the first 13 months. We previously reported effects upon the discharged patient as measured by the observed to expected length of stay (O:E LOS) and 30‐day readmission rate. We now assess the effect of our DBN initiative on the subsequent patient and hospital throughput. Our objectives for this study were: (1) to determine the effect of DBN on the admission arrival times and admissions per hour to the units, and (2) in a separate data collection and analysis, to determine if the increased DBN rate is sustainable. We hypothesize that DBN results in admissions arriving onto the units earlier in the day. We further hypothesize that because of this redistribution, DBN will level the load of admissions, reducing admissions per hour peaks that can occur late in the day.

METHODS

Study Design, Participants, and Setting

This is a pre‐/postretrospective analysis evaluating the effect of a previously described DBN intervention.[5] Two inpatient acute‐care medicine units at NYU Langone Medical Center's Tisch Hospital, a 725‐bed, urban, academic medical center, were included in the analysis. All patients admitted to the units underwent the intervention.

Intervention

The DBN intervention began with a multidisciplinary kickoff event in which all team members received education on the importance of DBN, a clear description of roles in the DBN process, and a corresponding checklist of responsibilities. The checklist was utilized at new afternoon interdisciplinary rounds intended to identify next‐day DBNs. Patients identified in afternoon interdisciplinary rounds were logged in a DBN website that generated twice‐daily automated emails to communicate the planned DBN list to frontline staff and key stakeholders. Daily, real‐time feedback on the DBN rate was provided to floor staff.

Measures

Admission Arrival Time

The arrival location and time to any hospital area (ED, radiology, inpatient medical unit) is recorded in the electronic medical record (Epic, Madison, WI) at the time the patient arrives by the patient unit assistant or unit clerk. We obtained the arrival time to each hospital unit throughout the patient's hospitalization for all patients arriving to the study units during their hospitalization between June 1, 2011 and March 4, 2012 (the baseline period) and March 5, 2012 and June 31, 2013 (the intervention period). Data from October 25, 2012 to the end of January 2013 were excluded due to hospital closure from Hurricane Sandy. These time periods and exclusions match those used in our previous DBN article.[5] To match that study's criteria, we excluded patients on the units in the patient class observation, inpatient hospice, and those patients whose discharge disposition was expired or hospice.

ED Admissions

All patients with a first inpatient unit location of ED and no other inpatient unit location prior to arrival on the study units were included in the ED admission analysis. Units that treat but do not provide long‐term boarding/housing of inpatientssuch as radiology, hemodialysis, and cardiac catheterizationwere not considered in determining ED admission status. Even if a patient had recorded arrival to those areas between ED and study unit arrival, these patients were considered ED admissions, as they were never admitted to another inpatient unit.

Transfers and Direct Admissions

All patients whose first inpatient unit location was the study units were included in the transfers and direct admissions analysis. Those patients who were recorded as coming from another inpatient unit (such as another medical, surgical, step‐down, intensive care, or other specialty unit) prior to study unit arrival were included as intrahospital transfers.

Level Load of Admissions

Level loading is a lean methodology term that describes reducing the unevenness in a production line to enhance efficiency.[11] We evaluated this by comparing the admissions per hour (density distribution) to the studied units in the pre‐ and postintervention periods.

Sustainability of the DBN Intervention

The DBN intervention, as described in our original article, continues uninterrupted. Using the same methodology, inclusion criteria, exclusion criteria, and data analysis previously described, we gathered the discharge date and time as recorded by the patient unit assistant for all patients discharged from the study units for the 18 months (July 1, 2013 to December 31, 2014) after our original article to evaluate the sustainability of our improvement in DBN rates.

Statistical Analysis

Median admission time to the floor was compared between the 2 time periods using the Wilcoxon rank sum test. This is a non parametric test of the null hypothesis that the two time periods have the same distributions of admission time to the floor. To evaluate statistical significance, each admission time is arranged in order of magnitude and assigned a rank. The sum of the ranks for each group is calculated and the smaller rank sum (the W statistic) is compared to an expected range of values based on the sample sizes. If this value is out of range then one can reject the null hypothesis. The density distributions of admissions during the 2 time periods were compared using the Kolmogorov‐Smirnov test. The 2‐sided Kolmogorov‐Smirnov test evaluates the maximum distance (D) between the distributions of 2 samples.[12] We chose this test because it evaluates differences between both the position and shape of the distributions of the samples.

RESULTS

Setting Characteristics

The units had an average occupancy rate of 86.8% for the duration of the study. The average number of total discharges per day was 9.8. The average absolute length of stay was 5.6 days.

Admission Arrival Time to the Unit

ED Admissions

A total of 6566 patients were admitted from the ED to the units, 2756 in the baseline period and 3810 in the intervention period. The median arrival time to the units of ED admissions grouped by hour of the day moved by 1 hour, from 5 pm to 4 pm from the baseline to intervention period, and this change was statistically significant (W=16,211,778, P<0.01) (Figure 1).

Figure 1
Timing of admissions from the emergency department by hour of the day. Count = number of patients.

Transfers and Direct Admissions

A total of 823 patients were transferred or directly admitted to the units, 310 in the baseline period and 513 in the intervention period. The median arrival time to the units grouped by hour of the day moved 1 hour from 5 pm to 4 pm, and this change was statistically significant (W=324,532, P<0.01) (Figure 2).

Figure 2
Timing of transfers and direct admissions by hour of the day. Count = number of patients.

Level Load of Admissions

In the baseline period, the highest density of ED admissions occurred during the 5‐hour period from 5 pm to 10 pm, when 42.3% of daily admissions arrived (Figure 3). In the intervention period, the highest density of admissions occurred during the 5‐hour period from 3 pm to 8 pm, when 40.0% of daily admissions arrived. The difference between the density distributions for the 2 time periods was found to be statistically significant using the Kolmogorov‐Smirnov test (D=0.03, P<0.01).

Figure 3
Density of emergency department (ED) admissions and transfers by hour of the day. Density = number of admissions per hour.

In the baseline period, the highest density of transfers and direct admissions occurred during the 5‐hour period from 3 pm to 8 pm, when 51.7% of daily admissions arrived (Figure 3). In the intervention time period, the highest density of transfers and direct admissions occurred during the 5‐hour time period from 2 pm to 7 pm, when 50.3% of daily admissions arrived. The difference between the density distributions of transfers and direct admissions for the 2 time periods was not statistically significant using the Kolmogorov‐Smirnov test (D=0.04, P=0.3).

Sustainability of the DBN Intervention

For the 18 months after the prior reported DBN intervention period, an additional 5505 total discharges were included for analysis. Of these, 1796 were DBN. The average DBN rate for the study units from March 5, 2012 until December 31, 2014 (the original intervention period plus the additional 18 months of new data) is 35% (Figure 4).

Figure 4
Calendar month percent discharge before noon (DBN).

DISCUSSION

The potential effects of DBN are multiple. By reducing the O:E LOS and allowing patients the time to acquire their medications, make follow‐up appointments, and ask questions while providers are still in the hospital, our DBN initiative impacts the discharged patient's quality, safety, and efficiency of care.[5] We now report how the DBN initiative potentially impacts the subsequent patient's efficiency of care and hospital throughput. In addition, we show that the DBN initiative is sustainable over years.

Over the same time course as our initial DBN intervention, we found a statistically significant change in the time when admitted patients arrive on the floor. This was true of those patients admitted through the ED and those directly admitted to the floor. In a complex hospital system with many factors both internal (bed cleaning, patient transportation) and external (natural variations in ED volume and acuity) affecting the timing of admissions, it is important to note that increasing the DBN rate correlates with a change in median admission arrival time. From a patient safety standpoint, any initiative that moves admissions away from evening and night hours and takes advantage of (usually more robust) day staffing is a potentially favorable intervention.[13]

We observed a statistically significant reduction of highest frequency peaks of ED admissions. It appears that opening beds up earlier in the day through DBN may help level the load of admissions from the ED. There was no effect on highest frequency peaks of transfer admissions to the floor. This may be due to the timing of transfers being dependent on factors other than bed availability, such as timing of transportation to the hospital or the timing of planned treatment.

We also found that the DBN intervention has created sustainable increases in the DBN rate. Since our initial publication, we have received direct communication from physicians, administrators and managers in 6 different states and 2 foreign countries asking for additional information or reporting that their hospitals are pursuing similar goals. Some of the most common questions asked include: Are your results sustained? and What do you think is a reasonable DBN goal? We have attempted to answer both of these questions. We previously reported improvement to an average DBN rate of 38% over the first 13 intervention months. With more time, we now see an absolute DBN rate of 35%. In November 2014, we restructured our medicine service to become geographic, so that the same group of doctors, trainees, nurses, care managers, and social workers care for patients on a single ward. Since this initiative, our DBN rate has climbed to greater than 40%. We hope to report further on this new intervention in the future. Similar hospital centers can consider using our experience on an inpatient acute‐care medical unit in an urban environment as a benchmark for setting hospital metric goals for early‐in‐the‐day discharge.

Several studies have previously reported on early‐in‐the‐day discharge initiatives. These were smaller studies that focused on descriptions of the type of intervention, including a discharge brunch on an obstetrics floor,[8] scheduled discharges,[6] in‐room displays of expected day and time of discharge,[9] and a physician‐centered discharge process.[7] Our study is substantially larger, focused on inpatient medicine units, and reports the effect of significant changes in DBN on patient and hospital metrics.

Our study had several limitations. The study is based in a single site, potentially limiting the generalizability of our findings. The hospital underwent tremendous change during the course of the intervention, including its temporary closure due to Hurricane Sandy. We cannot exclude effects related to shifts in volume and possible differences in the pre‐ and post‐time period patient populations. The prior study evaluated the population of discharged patients, but the admission analysis in this study involves the population of admitted patients. There may be slight differences in the populations due to the inclusion of patients who were admitted but not discharged from the units (for instance due to transfer after admission). Though the findings on admission arrival time correlate well with the increasing DBN rates, as they occur during the same time and in the same direction (earlier in the day), we are unable to conclude if the effect is causative. There were many interventions ongoing throughout the hospital to improve throughput, and these programs could have created local trends that confound our data. We are also unable to evaluate the clinical significance of a 1‐hour shift in median admission arrival time. Each hospital system must determine for itself if the time and resource investment in DBN is worth the change in admission timing described. We completed this analysis with the perspective of the inpatient medical unit experience, including the timing and number of admissions arriving to the units. We cannot exclude the possibility that changes in arrival times or boarding trends in the ED contribute to our findings.

CONCLUSION

In our hospital, a successful DBN initiative correlates with movement of ED admissions and transfers onto the inpatient units earlier in the day. There was a leveling of the load for ED admissions over the same time period. DBN continues to be an achievable hospital goal, and we provide a potential benchmark for similar hospitals.

Disclosure

Nothing to report.

It is thought that late afternoon hospital discharges create admission bottlenecks in the emergency department (ED).[1] As hospital occupancy increases, so too does ED boarding time.[2] Increased ED boarding time can result in increased length of stay (LOS)[3] and reduced patient and staff satisfaction.[4] Early in the day discharge programs are intended to improve hospital throughput.[5, 6, 7, 8, 9] Yet, ED admission timing is, in part, determined by external fluctuations in ED volume and acuity that early discharges do not impact.[10] We previously reported that high levels of discharge before noon (DBN) from inpatient medicine units is achievable through a multidisciplinary intervention.[5] We now evaluate the effect of this intervention upon admission patterns and the sustainability of the DBN initiative.

The DBN intervention consisted of afternoon interdisciplinary rounds, a checklist of team members' responsibilities, a standardized electronic communication tool, and daily feedback on the DBN rate.[5] The intervention resulted in an increase in the DBN rate from 11% to 38% in the first 13 months. We previously reported effects upon the discharged patient as measured by the observed to expected length of stay (O:E LOS) and 30‐day readmission rate. We now assess the effect of our DBN initiative on the subsequent patient and hospital throughput. Our objectives for this study were: (1) to determine the effect of DBN on the admission arrival times and admissions per hour to the units, and (2) in a separate data collection and analysis, to determine if the increased DBN rate is sustainable. We hypothesize that DBN results in admissions arriving onto the units earlier in the day. We further hypothesize that because of this redistribution, DBN will level the load of admissions, reducing admissions per hour peaks that can occur late in the day.

METHODS

Study Design, Participants, and Setting

This is a pre‐/postretrospective analysis evaluating the effect of a previously described DBN intervention.[5] Two inpatient acute‐care medicine units at NYU Langone Medical Center's Tisch Hospital, a 725‐bed, urban, academic medical center, were included in the analysis. All patients admitted to the units underwent the intervention.

Intervention

The DBN intervention began with a multidisciplinary kickoff event in which all team members received education on the importance of DBN, a clear description of roles in the DBN process, and a corresponding checklist of responsibilities. The checklist was utilized at new afternoon interdisciplinary rounds intended to identify next‐day DBNs. Patients identified in afternoon interdisciplinary rounds were logged in a DBN website that generated twice‐daily automated emails to communicate the planned DBN list to frontline staff and key stakeholders. Daily, real‐time feedback on the DBN rate was provided to floor staff.

Measures

Admission Arrival Time

The arrival location and time to any hospital area (ED, radiology, inpatient medical unit) is recorded in the electronic medical record (Epic, Madison, WI) at the time the patient arrives by the patient unit assistant or unit clerk. We obtained the arrival time to each hospital unit throughout the patient's hospitalization for all patients arriving to the study units during their hospitalization between June 1, 2011 and March 4, 2012 (the baseline period) and March 5, 2012 and June 31, 2013 (the intervention period). Data from October 25, 2012 to the end of January 2013 were excluded due to hospital closure from Hurricane Sandy. These time periods and exclusions match those used in our previous DBN article.[5] To match that study's criteria, we excluded patients on the units in the patient class observation, inpatient hospice, and those patients whose discharge disposition was expired or hospice.

ED Admissions

All patients with a first inpatient unit location of ED and no other inpatient unit location prior to arrival on the study units were included in the ED admission analysis. Units that treat but do not provide long‐term boarding/housing of inpatientssuch as radiology, hemodialysis, and cardiac catheterizationwere not considered in determining ED admission status. Even if a patient had recorded arrival to those areas between ED and study unit arrival, these patients were considered ED admissions, as they were never admitted to another inpatient unit.

Transfers and Direct Admissions

All patients whose first inpatient unit location was the study units were included in the transfers and direct admissions analysis. Those patients who were recorded as coming from another inpatient unit (such as another medical, surgical, step‐down, intensive care, or other specialty unit) prior to study unit arrival were included as intrahospital transfers.

Level Load of Admissions

Level loading is a lean methodology term that describes reducing the unevenness in a production line to enhance efficiency.[11] We evaluated this by comparing the admissions per hour (density distribution) to the studied units in the pre‐ and postintervention periods.

Sustainability of the DBN Intervention

The DBN intervention, as described in our original article, continues uninterrupted. Using the same methodology, inclusion criteria, exclusion criteria, and data analysis previously described, we gathered the discharge date and time as recorded by the patient unit assistant for all patients discharged from the study units for the 18 months (July 1, 2013 to December 31, 2014) after our original article to evaluate the sustainability of our improvement in DBN rates.

Statistical Analysis

Median admission time to the floor was compared between the 2 time periods using the Wilcoxon rank sum test. This is a non parametric test of the null hypothesis that the two time periods have the same distributions of admission time to the floor. To evaluate statistical significance, each admission time is arranged in order of magnitude and assigned a rank. The sum of the ranks for each group is calculated and the smaller rank sum (the W statistic) is compared to an expected range of values based on the sample sizes. If this value is out of range then one can reject the null hypothesis. The density distributions of admissions during the 2 time periods were compared using the Kolmogorov‐Smirnov test. The 2‐sided Kolmogorov‐Smirnov test evaluates the maximum distance (D) between the distributions of 2 samples.[12] We chose this test because it evaluates differences between both the position and shape of the distributions of the samples.

RESULTS

Setting Characteristics

The units had an average occupancy rate of 86.8% for the duration of the study. The average number of total discharges per day was 9.8. The average absolute length of stay was 5.6 days.

Admission Arrival Time to the Unit

ED Admissions

A total of 6566 patients were admitted from the ED to the units, 2756 in the baseline period and 3810 in the intervention period. The median arrival time to the units of ED admissions grouped by hour of the day moved by 1 hour, from 5 pm to 4 pm from the baseline to intervention period, and this change was statistically significant (W=16,211,778, P<0.01) (Figure 1).

Figure 1
Timing of admissions from the emergency department by hour of the day. Count = number of patients.

Transfers and Direct Admissions

A total of 823 patients were transferred or directly admitted to the units, 310 in the baseline period and 513 in the intervention period. The median arrival time to the units grouped by hour of the day moved 1 hour from 5 pm to 4 pm, and this change was statistically significant (W=324,532, P<0.01) (Figure 2).

Figure 2
Timing of transfers and direct admissions by hour of the day. Count = number of patients.

Level Load of Admissions

In the baseline period, the highest density of ED admissions occurred during the 5‐hour period from 5 pm to 10 pm, when 42.3% of daily admissions arrived (Figure 3). In the intervention period, the highest density of admissions occurred during the 5‐hour period from 3 pm to 8 pm, when 40.0% of daily admissions arrived. The difference between the density distributions for the 2 time periods was found to be statistically significant using the Kolmogorov‐Smirnov test (D=0.03, P<0.01).

Figure 3
Density of emergency department (ED) admissions and transfers by hour of the day. Density = number of admissions per hour.

In the baseline period, the highest density of transfers and direct admissions occurred during the 5‐hour period from 3 pm to 8 pm, when 51.7% of daily admissions arrived (Figure 3). In the intervention time period, the highest density of transfers and direct admissions occurred during the 5‐hour time period from 2 pm to 7 pm, when 50.3% of daily admissions arrived. The difference between the density distributions of transfers and direct admissions for the 2 time periods was not statistically significant using the Kolmogorov‐Smirnov test (D=0.04, P=0.3).

Sustainability of the DBN Intervention

For the 18 months after the prior reported DBN intervention period, an additional 5505 total discharges were included for analysis. Of these, 1796 were DBN. The average DBN rate for the study units from March 5, 2012 until December 31, 2014 (the original intervention period plus the additional 18 months of new data) is 35% (Figure 4).

Figure 4
Calendar month percent discharge before noon (DBN).

DISCUSSION

The potential effects of DBN are multiple. By reducing the O:E LOS and allowing patients the time to acquire their medications, make follow‐up appointments, and ask questions while providers are still in the hospital, our DBN initiative impacts the discharged patient's quality, safety, and efficiency of care.[5] We now report how the DBN initiative potentially impacts the subsequent patient's efficiency of care and hospital throughput. In addition, we show that the DBN initiative is sustainable over years.

Over the same time course as our initial DBN intervention, we found a statistically significant change in the time when admitted patients arrive on the floor. This was true of those patients admitted through the ED and those directly admitted to the floor. In a complex hospital system with many factors both internal (bed cleaning, patient transportation) and external (natural variations in ED volume and acuity) affecting the timing of admissions, it is important to note that increasing the DBN rate correlates with a change in median admission arrival time. From a patient safety standpoint, any initiative that moves admissions away from evening and night hours and takes advantage of (usually more robust) day staffing is a potentially favorable intervention.[13]

We observed a statistically significant reduction of highest frequency peaks of ED admissions. It appears that opening beds up earlier in the day through DBN may help level the load of admissions from the ED. There was no effect on highest frequency peaks of transfer admissions to the floor. This may be due to the timing of transfers being dependent on factors other than bed availability, such as timing of transportation to the hospital or the timing of planned treatment.

We also found that the DBN intervention has created sustainable increases in the DBN rate. Since our initial publication, we have received direct communication from physicians, administrators and managers in 6 different states and 2 foreign countries asking for additional information or reporting that their hospitals are pursuing similar goals. Some of the most common questions asked include: Are your results sustained? and What do you think is a reasonable DBN goal? We have attempted to answer both of these questions. We previously reported improvement to an average DBN rate of 38% over the first 13 intervention months. With more time, we now see an absolute DBN rate of 35%. In November 2014, we restructured our medicine service to become geographic, so that the same group of doctors, trainees, nurses, care managers, and social workers care for patients on a single ward. Since this initiative, our DBN rate has climbed to greater than 40%. We hope to report further on this new intervention in the future. Similar hospital centers can consider using our experience on an inpatient acute‐care medical unit in an urban environment as a benchmark for setting hospital metric goals for early‐in‐the‐day discharge.

Several studies have previously reported on early‐in‐the‐day discharge initiatives. These were smaller studies that focused on descriptions of the type of intervention, including a discharge brunch on an obstetrics floor,[8] scheduled discharges,[6] in‐room displays of expected day and time of discharge,[9] and a physician‐centered discharge process.[7] Our study is substantially larger, focused on inpatient medicine units, and reports the effect of significant changes in DBN on patient and hospital metrics.

Our study had several limitations. The study is based in a single site, potentially limiting the generalizability of our findings. The hospital underwent tremendous change during the course of the intervention, including its temporary closure due to Hurricane Sandy. We cannot exclude effects related to shifts in volume and possible differences in the pre‐ and post‐time period patient populations. The prior study evaluated the population of discharged patients, but the admission analysis in this study involves the population of admitted patients. There may be slight differences in the populations due to the inclusion of patients who were admitted but not discharged from the units (for instance due to transfer after admission). Though the findings on admission arrival time correlate well with the increasing DBN rates, as they occur during the same time and in the same direction (earlier in the day), we are unable to conclude if the effect is causative. There were many interventions ongoing throughout the hospital to improve throughput, and these programs could have created local trends that confound our data. We are also unable to evaluate the clinical significance of a 1‐hour shift in median admission arrival time. Each hospital system must determine for itself if the time and resource investment in DBN is worth the change in admission timing described. We completed this analysis with the perspective of the inpatient medical unit experience, including the timing and number of admissions arriving to the units. We cannot exclude the possibility that changes in arrival times or boarding trends in the ED contribute to our findings.

CONCLUSION

In our hospital, a successful DBN initiative correlates with movement of ED admissions and transfers onto the inpatient units earlier in the day. There was a leveling of the load for ED admissions over the same time period. DBN continues to be an achievable hospital goal, and we provide a potential benchmark for similar hospitals.

Disclosure

Nothing to report.

References
  1. Khanna S, Boyle J, Good N, Lind J. Impact of admission and discharge peak times on hospital overcrowding. Stud Health Technol Inform. 2011;168:8288.
  2. Rathlev NK, Obendorfer D, White LF, et al. Time series analysis of emergency department length of stay per 8‐hour shift. West J Emerg Med. 2012;13(2):163168.
  3. White BA, Biddinger PD, Chang Y, Grabowski B, Carignan S, Brown DF. Boarding inpatients in the emergency department increases discharged patient length of stay. J Emerg Med. 2013;44(1):230235.
  4. Derlet RW, Richards JR. Overcrowding in the nation's emergency departments: complex causes and disturbing effects. Ann Emerg Med. 2000;35(1):6368.
  5. Wertheimer B, Jacobs RE, Bailey M, et al. Discharge before noon: an achievable hospital goal. J Hosp Med. 2014;9(4):210214.
  6. Bergstrom J FL, Quinn M, Wheeler H. All roads lead to scheduled discharges. Nursing. 2008;38(12):6163.
  7. Kravet SJ, Levine RB, Rubin HR, Wright SM. Discharging patients earlier in the day: a concept worth evaluating. Health Care Manag (Frederick). 2007;26(2):142146.
  8. Lucia MA, Mullaly LM. The discharge brunch: reducing chaos and increasing smiles on the OB unit. Nurs Womens Health. 2009;13(5):402409.
  9. Manning DM, Tammel KJ, Blegen RN, et al. In‐room display of day and time patient is anticipated to leave hospital: a “discharge appointment”. J Hosp Med. 2007;2(1):1316.
  10. Arkun A, Briggs WM, Patel S, Datillo PA, Bove J, Birkhahn RH. Emergency department crowding: factors influencing flow. West J Emerg Med. 2010;11(1):1015.
  11. Liker JK. The Toyota Way: 14 Management Principles From the World's Greatest Manufacturer. New York, NY: McGraw‐Hill; 2004.
  12. Thas O. Comparing Distributions. New York, NY: Springer; 2010.
  13. Peberdy MA, Ornato JP, Larkin GL, et al. Survival from in‐hospital cardiac arrest during nights and weekends. JAMA. 2008;299(7):785792.
References
  1. Khanna S, Boyle J, Good N, Lind J. Impact of admission and discharge peak times on hospital overcrowding. Stud Health Technol Inform. 2011;168:8288.
  2. Rathlev NK, Obendorfer D, White LF, et al. Time series analysis of emergency department length of stay per 8‐hour shift. West J Emerg Med. 2012;13(2):163168.
  3. White BA, Biddinger PD, Chang Y, Grabowski B, Carignan S, Brown DF. Boarding inpatients in the emergency department increases discharged patient length of stay. J Emerg Med. 2013;44(1):230235.
  4. Derlet RW, Richards JR. Overcrowding in the nation's emergency departments: complex causes and disturbing effects. Ann Emerg Med. 2000;35(1):6368.
  5. Wertheimer B, Jacobs RE, Bailey M, et al. Discharge before noon: an achievable hospital goal. J Hosp Med. 2014;9(4):210214.
  6. Bergstrom J FL, Quinn M, Wheeler H. All roads lead to scheduled discharges. Nursing. 2008;38(12):6163.
  7. Kravet SJ, Levine RB, Rubin HR, Wright SM. Discharging patients earlier in the day: a concept worth evaluating. Health Care Manag (Frederick). 2007;26(2):142146.
  8. Lucia MA, Mullaly LM. The discharge brunch: reducing chaos and increasing smiles on the OB unit. Nurs Womens Health. 2009;13(5):402409.
  9. Manning DM, Tammel KJ, Blegen RN, et al. In‐room display of day and time patient is anticipated to leave hospital: a “discharge appointment”. J Hosp Med. 2007;2(1):1316.
  10. Arkun A, Briggs WM, Patel S, Datillo PA, Bove J, Birkhahn RH. Emergency department crowding: factors influencing flow. West J Emerg Med. 2010;11(1):1015.
  11. Liker JK. The Toyota Way: 14 Management Principles From the World's Greatest Manufacturer. New York, NY: McGraw‐Hill; 2004.
  12. Thas O. Comparing Distributions. New York, NY: Springer; 2010.
  13. Peberdy MA, Ornato JP, Larkin GL, et al. Survival from in‐hospital cardiac arrest during nights and weekends. JAMA. 2008;299(7):785792.
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Address for correspondence and reprint requests: Benjamin Wertheimer, MD, 550 First Ave., Tisch Hospital, Room 1803, New York, NY 10016; Telephone: 646‐501‐6939; Fax: 212‐263‐6022; E‐mail: [email protected]
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Nebulized Bronchodilator Instead of MDI

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Nebulized bronchodilators instead of metered‐dose inhalers for obstructive pulmonary symptoms

The Things We Do for No Reason (TWDFNR) series reviews practices which have become common parts of hospital care but which may provide little value to our patients. Practices reviewed in the TWDFNR series do not represent black and white conclusions or clinical practice standards, but are meant as a starting place for research and active discussions among hospitalists and patients. We invite you to be part of that discussion. https://www.choosingwisely.org/

CASE PRESENTATION

A 54‐year‐old woman presented to the emergency department (ED) with shortness of breath. She reported that her primary care physician diagnosed her with chronic obstructive pulmonary disease (COPD). Her physician had prescribed her an albuterol inhaler to use as needed for shortness of breath. Over the past few weeks she had been trying to use the inhaler, but she noted that it did not seem to help her increasing wheezing, coughing, and sputum production. In the ED, she received continuous albuterol treatments via nebulizer, Solu‐Medrol 125 mg intravenously, antibiotics, and a chest x‐ray. She was admitted to the hospital medicine service for COPD exacerbation and started on nebulized bronchodilator treatments every 4 hours. By the fourth day of her hospital stay, she was discharged to home with an albuterol inhaler, oral prednisone, oral doxycycline, and a follow‐up appointment. Dedicated patient education regarding proper inhaler administration did not occur during hospitalization.

WHY YOU MIGHT THINK NEBULIZED TREATMENTS IN INPATIENTS ARE HELPFUL

Inhaled bronchodilators are a mainstay of therapy for acute obstructive pulmonary diseases, including COPD and asthma exacerbations.[1, 2] Inhaled bronchodilators may be delivered by metered‐dose inhalers (MDIs) or via wet nebulizers powered by compressed air or oxygen. Current practice patterns in EDs and hospital wards tend to favor the use of nebulizers due to many apparent advantages of these devices.[3] For instance, nebulizers do not require any special inhalation technique and can be effectively used by patients at any age.[3, 4] There is also a common perception that nebulizers are more effective, possibly stemming from the assumption that hospitalized patients have already failed their outpatient MDI therapy and an almost mystical belief in the healing power of mist. Moreover, many clinicians have been trained to routinely use nebulizer therapies and may lack sufficient knowledge or comfort about the relative efficacy and equivalence dosing of MDI therapies.

WHY NEBULIZERS ARE NOT BETTER THAN MDIs FOR PATIENTS HOSPITALIZED WITH OBSTRUCTIVE PULMONARY SYMPTOMS

Decades of research support that MDIs are effective, efficient, and less costly (depending on circumstances) than nebulizers for the routine treatment of obstructive pulmonary exacerbations.[3, 4, 5, 6, 7, 8, 9, 10, 11] The clinical effectiveness of MDIs has been shown in studies across populations of adults with acute COPD symptoms,[3, 4, 7, 8] as well as children and adults with asthma exacerbations.[3, 4, 5, 6, 9, 10] A 2005 joint report by the American College of Chest Physicians (ACCP) and the American College of Asthma, Allergy and Immunology (ACAAI), concluded none of the pooled meta‐analyses showed a significant difference between devices in any efficacy outcome in any patient group for each of the clinical settings.[4] Many different outcomes have been investigated, including forced expiratory volumes (FEV), peak flows, symptoms and specific symptom scores, and physical findings.[4]

Compared to MDIs, there are a number of drawbacks to the use of nebulizers: nebulizers are more expensive to buy and maintain, are less portable, and take longer to set up, use, and clean following each use.[12] In addition, nebulizers have been associated with greater increases in heart rate and tremors compared to MDIs, suggesting nebulizers lead to higher systemically absorbed ‐agonist doses.[4]

Of note, nearly all of the clinical effectiveness studies administered MDIs with a valved holding chamber or spacer, facilitating the delivery of drug to the airways.[3, 4] Although valved holding chambers are commonly referred to as a spacer, a true spacer does not have a valve and is rarely used today.[12]

THE EVIDENCE EXAMINING NEBULIZERS VERSUS MDIs IN PATIENTS WITH ASTHMA OR COPD EXACERBATIONS

A 2013 Cochrane review sought to establish the relative efficacy of MDIs with holding chambers versus nebulizers for children and adults who presented to a community setting or emergency department with acute asthma.[6] The review included a total of 1897 children and 729 adults in 39 randomized controlled trials. The authors judged the overall evidence to be of moderate quality. Children with acute asthma treated with MDIs in the ED had shorter lengths of stay in the ED (70 minutes vs 103 minutes), similar peak flow and FEV measurements, lower heart rates, and less tremor compared to children treated with nebulizers.[5, 6] There were no significant differences found between devices for the treatment of adult patients with asthma.[6]

In a separate double‐blind, randomized, placebo‐controlled study evaluating albuterol administered by nebulizer versus MDI with spacer for children <2 years old presenting to an ED with wheezing, the use of MDIs with a spacer and facemask was equally efficacious and may have led to fewer hospital admissions.[10]

Mandelberg et al. performed a double‐blind, randomized, placebo‐controlled trial for unselected adult patients presenting to an ED with obstructive pulmonary symptoms.[8] Patients received either 2 puffs of a placebo MDI with a spacer along with nebulized salbutamol 0.5 mL in 1.5 mL saline solution (n=25), or a salbutamol MDI along with a nebulized placebo saline solution (n=25). Treatments were repeated every 15 minutes up to 3 times, unless side effects occurred. Spirometric measurements were performed following each treatment. No differences were seen between the groups at any point during the study period. The authors concluded, Even in the setting of the unselected group of patient referrals to the [Department of Emergency Medicine] for episodes of severe airflow limitation, the clinical and objective bronchodilator responses to the administration of salbutamol are independent of the method of delivery: MDI with large spacer or aerosol nebulization.[8]

There are surprisingly few studies examining the use of nebulizers versus MDIs in the inpatient setting for both children and adults. Dolovich et al. reviewed 6 studies that included 253 total patients and reported no significant differences in pulmonary function between devices.[4] Based on these findings, the ACCP/ACAAI group recommended both nebulizers and MDIs with spacers/holding chambers are appropriate for use in the inpatient setting. Quality of evidence: good.[4]

WHY USE MDIs FOR INPATIENTS

If MDI and nebulizer treatments are equally effective, why change current practice? The use of MDIs, rather than nebulizers, in hospitals could lead to fewer side effects such as tachycardia, arrhythmias, and tremors. MDIs are also more portable and do not require specialized set‐up. Furthermore, MDI administrations during hospitalization may provide a golden opportunity to have respiratory therapists, pharmacists, or other health professionals spend time teaching patients proper inhaler usage, rather than providing time‐consuming nebulizer treatments.[13] In a recent study, approximately 86% of hospitalized patients with asthma or COPD could not demonstrate appropriate use of an MDI. However, 100% of patients were able to achieve mastery following a short teach‐back session.[14] It is conceivable that transitioning patients to MDIs earlier during hospitalization and providing them with education regarding proper MDI administration could instill confidence in their use of inhalers and result in downstream effects such as shorter lengths of stay, less frequent hospital readmissions, or improved quality of life.

MDI use may result in cost savings in certain settings, although the relative costs of nebulizer versus MDI treatments depends on many institution‐specific factors. Such factors include the institutional policies on who delivers the nebulizer or the MDI and how they are compensated and staffed. For example in the Nebs No More After 24 program initiated at the University of California, San Francisco, the vast majority of the realized cost savings are due to the reduction in respiratory therapist time spent delivering MDIs, which reflects the local policies and compensation structure.[13] Previous inpatient interventions to convert from nebulizers to MDIs also showed cost savings resulting from decreased labor needs.[15] In some hospitals, nurses deliver nebulizer treatments, whereas in others only respiratory therapists are allowed to provide nebulizers. Moreover, whether the MDI can go home with the patient upon discharge depends on whether the hospital has a dispensing pharmacy or not. Formal economic evaluations specific to the local institution are necessary.

WHAT WE SHOULD DO INSTEAD: ENCOURAGE THE USE OF MDIs FOR INPATIENTS

For effective inpatient MDI treatments, MDI technique must be good. Thus, it is vital to enlist the right people to provide proper MDI teaching and supervision. Respiratory therapists are generally trained for this task, and may be complemented by appropriately trained physicians, nurses, or pharmacists. Many institutions have successfully implemented respiratory therapist‐driven protocols for the administration of MDIs, which has led to measurable improvements in the utilization of appropriate respiratory care resources.[15, 16] At University of California, San Francisco, this was accomplished by recruiting respiratory therapists and nurses to help support the transition of patients from nebulizers to MDIs and to provide bedside teaching on proper MDI usage. The institution then launched a Nebs No More After 24 campaign that sought to transition patients from nebulizers to MDIs within 24 hours of hospitalization. This campaign included an educational program for physicians, prepared facilitator guides to assist attending physicians with teaching about the new initiative, publicity efforts including pens and strategically placed posters, and regular feedback regarding nebulizer utilization on the pilot ward. Although the evidence suggests that patients can be started on MDIs immediately upon presentation to the ED, the UCSF campaign focused on transitioning patients within 24 hours so to alleviate concerns about transitions in care between the ED and the medical ward, as well as between overnight and day teams. MDIs are only as or more effective than nebulizers if the correct administration technique is employed. The 24‐hour transition period allows for MDI teaching and transition during regular daytime hours.

Inpatient use of nebulizers may be more appropriate than MDIs for patients with dementia or altered mental status, as well as those in extreme distress resulting in an inability to coordinate inhaler usage. Very low health literacy may be an additional barrier to appropriate MDI teaching and usage.

RECOMMENDATIONS

In patients with obstructive pulmonary symptoms, transition patients from nebulizers to MDIs early in their hospital course, unless the patient is unable to use an inhaler due to altered mental status, dementia, or other circumstances. Ensure that patients are instructed and supervised on proper MDI technique. Enlisting respiratory therapists and appropriately trained staff (pharmacists, nurses, physicians) is key to the successful use of MDIs. Frequency and dosage of MDIs used should be comparable to that of nebulized treatments. Although studies have used a relatively wide range of albuterol MDI dosing, prior programs have determined a dose of albuterol 4 puffs via MDI as being equivalent to the standard albuterol 2.5 mg nebulizer dosage.[17, 18] Some studies have advocated for using a range of 2 to 10 puffs albuterol MDI, with the actual dose based on clinical response.[17] One study in children with mild acute asthma found that 2 puffs of albuterol by MDI was just as effective as higher doses delivered by MDI (610 puffs) or by nebulizer.[19]

CONCLUSION

MDIs with holding chambers are clinically equivalent to nebulizer therapy for the treatment of both children and adults with obstructive pulmonary symptoms, as long as MDI technique and MDI dosing is adequate. This is based on good data in the ED setting but fewer studies in adult inpatients. There are a number of advantages to the use of inpatient MDIs over nebulizers; MDIs are more portable, often less expensive to use, may result in fewer side effects, and will hopefully improve outpatient MDI technique. The delivery of MDIs during hospitalization should be accompanied with patient education regarding proper administration technique.

Disclosure

Nothing to report.

Do you think this is a low‐value practice? Is this truly a Thing We Do for No Reason? Share what you do in your practice and join in the conversation online by retweeting it on Twitter (#TWDFNR) and Liking It on Facebook. We invite you to propose ideas for other Things We Do for No Reason topics by emailing [email protected]

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References
  1. Global Initiative for Chronic Obstructive Lung Disease (GOLD). Global strategy for the diagnosis, management, and prevention of COPD. Available at: http://www.goldcopd.org/guidelines‐global‐strategy‐for‐diagnosis‐management.html. Updated January 2015. Accessed September 25, 2014.
  2. National Heart Lung and Blood Institute. National Asthma Education and Prevention Program. Expert panel report 3: guidelines for the diagnosis and management of asthma. Available at: http://www.nhlbi.nih.gov/guidelines/asthma/asthgdln.htm. Published 2007. Updated April 2012. Accessed September 25, 2014.
  3. Turner MO, Patel A, Ginsburg S, FitzGerald JM. Bronchodilator delivery in acute airflow obstruction. A meta‐analysis. Arch Intern Med. 1997;157(15):17361744.
  4. Dolovich MB, Ahrens RC, Hess DR, et al. Device selection and outcomes of aerosol therapy: Evidence‐based guidelines: American College of Chest Physicians/American College of Asthma, Allergy, and Immunology. Chest. 2005;127(1):335371.
  5. Castro‐Rodriguez JA, Rodrigo GJ. Beta‐agonists through metered‐dose inhaler with valved holding chamber versus nebulizer for acute exacerbation of wheezing or asthma in children under 5 years of age: a systematic review with meta‐analysis. J Pediatr. 2004;145(2):172177.
  6. Cates CJ, Welsh EJ, Rowe BH. Holding chambers (spacers) versus nebulisers for beta‐agonist treatment of acute asthma. Cochrane Database Syst Rev. 2013;9:CD000052.
  7. Berry RB, Shinto RA, Wong FH, Despars JA, Light RW. Nebulizer vs spacer for bronchodilator delivery in patients hospitalized for acute exacerbations of COPD. Chest. 1989;96(6):12411246.
  8. Mandelberg A, Chen E, Noviski N, Priel IE. Nebulized wet aerosol treatment in emergency department—is it essential? Comparison with large spacer device for metered‐dose inhaler. Chest. 1997;112(6):15011505.
  9. Deerojanawong J, Manuyakorn W, Prapphal N, Harnruthakorn C, Sritippayawan S, Samransamruajkit R. Randomized controlled trial of salbutamol aerosol therapy via metered dose inhaler‐spacer vs. jet nebulizer in young children with wheezing. Pediatr Pulmonol. 2005;39(5):466472.
  10. Delgado A, Chou KJ, Silver EJ, Crain EF. Nebulizers vs metered‐dose inhalers with spacers for bronchodilator therapy to treat wheezing in children aged 2 to 24 months in a pediatric emergency department. Arch Pediatr Adolesc Med. 2003;157(1):7680.
  11. Turner MO, Gafni A, Swan D, FitzGerald JM. A review and economic evaluation of bronchodilator delivery methods in hospitalized patients. Arch Intern Med. 1996;156(18):21132118.
  12. Rottier BL, Rubin BK. Asthma medication delivery: mists and myths. Paediatr Respir Rev. 2013;14(2):112118.
  13. Moriates C, Novelero M, Quinn K, Khanna R, Mourad M. “Nebs no more after 24”: a pilot program to improve the use of appropriate respiratory therapies. JAMA Intern Med. 2013;173(17):16471648.
  14. Press VG, Arora VM, Shah LM, et al. Misuse of respiratory inhalers in hospitalized patients with asthma or COPD. J Gen Intern Med. 2011;26(6):635642.
  15. Tenholder MF, Bryson MJ, Whitlock WL. A model for conversion from small volume nebulizer to metered dose inhaler aerosol therapy. Chest. 1992;101(3):634637.
  16. Kallam A, Meyerink K, Modrykamien AM. Physician‐ordered aerosol therapy versus respiratory therapist‐driven aerosol protocol: the effect on resource utilization. Respir Care. 2013;58(3):431437.
  17. Hendeles L, Hatton RC, Coons TJ, Carlson L. Automatic replacement of albuterol nebulizer therapy by metered‐dose inhaler and valved holding chamber. Am J Health Syst Pharm. 2005;62(10):10531061.
  18. Salyer JW, DiBlasi RM, Crotwell DN, Cowan CA, Carter ER. The conversion to metered‐dose inhaler with valved holding chamber to administer inhaled albuterol: a pediatric hospital experience. Respir Care. 2008;53(3):338345.
  19. Schuh S, Johnson DW, Stephens D, Callahan S, Winders P, Canny GJ. Comparison of albuterol delivered by a metered dose inhaler with spacer versus a nebulizer in children with mild acute asthma. J Pediatr. 1999;135(1):2227.
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The Things We Do for No Reason (TWDFNR) series reviews practices which have become common parts of hospital care but which may provide little value to our patients. Practices reviewed in the TWDFNR series do not represent black and white conclusions or clinical practice standards, but are meant as a starting place for research and active discussions among hospitalists and patients. We invite you to be part of that discussion. https://www.choosingwisely.org/

CASE PRESENTATION

A 54‐year‐old woman presented to the emergency department (ED) with shortness of breath. She reported that her primary care physician diagnosed her with chronic obstructive pulmonary disease (COPD). Her physician had prescribed her an albuterol inhaler to use as needed for shortness of breath. Over the past few weeks she had been trying to use the inhaler, but she noted that it did not seem to help her increasing wheezing, coughing, and sputum production. In the ED, she received continuous albuterol treatments via nebulizer, Solu‐Medrol 125 mg intravenously, antibiotics, and a chest x‐ray. She was admitted to the hospital medicine service for COPD exacerbation and started on nebulized bronchodilator treatments every 4 hours. By the fourth day of her hospital stay, she was discharged to home with an albuterol inhaler, oral prednisone, oral doxycycline, and a follow‐up appointment. Dedicated patient education regarding proper inhaler administration did not occur during hospitalization.

WHY YOU MIGHT THINK NEBULIZED TREATMENTS IN INPATIENTS ARE HELPFUL

Inhaled bronchodilators are a mainstay of therapy for acute obstructive pulmonary diseases, including COPD and asthma exacerbations.[1, 2] Inhaled bronchodilators may be delivered by metered‐dose inhalers (MDIs) or via wet nebulizers powered by compressed air or oxygen. Current practice patterns in EDs and hospital wards tend to favor the use of nebulizers due to many apparent advantages of these devices.[3] For instance, nebulizers do not require any special inhalation technique and can be effectively used by patients at any age.[3, 4] There is also a common perception that nebulizers are more effective, possibly stemming from the assumption that hospitalized patients have already failed their outpatient MDI therapy and an almost mystical belief in the healing power of mist. Moreover, many clinicians have been trained to routinely use nebulizer therapies and may lack sufficient knowledge or comfort about the relative efficacy and equivalence dosing of MDI therapies.

WHY NEBULIZERS ARE NOT BETTER THAN MDIs FOR PATIENTS HOSPITALIZED WITH OBSTRUCTIVE PULMONARY SYMPTOMS

Decades of research support that MDIs are effective, efficient, and less costly (depending on circumstances) than nebulizers for the routine treatment of obstructive pulmonary exacerbations.[3, 4, 5, 6, 7, 8, 9, 10, 11] The clinical effectiveness of MDIs has been shown in studies across populations of adults with acute COPD symptoms,[3, 4, 7, 8] as well as children and adults with asthma exacerbations.[3, 4, 5, 6, 9, 10] A 2005 joint report by the American College of Chest Physicians (ACCP) and the American College of Asthma, Allergy and Immunology (ACAAI), concluded none of the pooled meta‐analyses showed a significant difference between devices in any efficacy outcome in any patient group for each of the clinical settings.[4] Many different outcomes have been investigated, including forced expiratory volumes (FEV), peak flows, symptoms and specific symptom scores, and physical findings.[4]

Compared to MDIs, there are a number of drawbacks to the use of nebulizers: nebulizers are more expensive to buy and maintain, are less portable, and take longer to set up, use, and clean following each use.[12] In addition, nebulizers have been associated with greater increases in heart rate and tremors compared to MDIs, suggesting nebulizers lead to higher systemically absorbed ‐agonist doses.[4]

Of note, nearly all of the clinical effectiveness studies administered MDIs with a valved holding chamber or spacer, facilitating the delivery of drug to the airways.[3, 4] Although valved holding chambers are commonly referred to as a spacer, a true spacer does not have a valve and is rarely used today.[12]

THE EVIDENCE EXAMINING NEBULIZERS VERSUS MDIs IN PATIENTS WITH ASTHMA OR COPD EXACERBATIONS

A 2013 Cochrane review sought to establish the relative efficacy of MDIs with holding chambers versus nebulizers for children and adults who presented to a community setting or emergency department with acute asthma.[6] The review included a total of 1897 children and 729 adults in 39 randomized controlled trials. The authors judged the overall evidence to be of moderate quality. Children with acute asthma treated with MDIs in the ED had shorter lengths of stay in the ED (70 minutes vs 103 minutes), similar peak flow and FEV measurements, lower heart rates, and less tremor compared to children treated with nebulizers.[5, 6] There were no significant differences found between devices for the treatment of adult patients with asthma.[6]

In a separate double‐blind, randomized, placebo‐controlled study evaluating albuterol administered by nebulizer versus MDI with spacer for children <2 years old presenting to an ED with wheezing, the use of MDIs with a spacer and facemask was equally efficacious and may have led to fewer hospital admissions.[10]

Mandelberg et al. performed a double‐blind, randomized, placebo‐controlled trial for unselected adult patients presenting to an ED with obstructive pulmonary symptoms.[8] Patients received either 2 puffs of a placebo MDI with a spacer along with nebulized salbutamol 0.5 mL in 1.5 mL saline solution (n=25), or a salbutamol MDI along with a nebulized placebo saline solution (n=25). Treatments were repeated every 15 minutes up to 3 times, unless side effects occurred. Spirometric measurements were performed following each treatment. No differences were seen between the groups at any point during the study period. The authors concluded, Even in the setting of the unselected group of patient referrals to the [Department of Emergency Medicine] for episodes of severe airflow limitation, the clinical and objective bronchodilator responses to the administration of salbutamol are independent of the method of delivery: MDI with large spacer or aerosol nebulization.[8]

There are surprisingly few studies examining the use of nebulizers versus MDIs in the inpatient setting for both children and adults. Dolovich et al. reviewed 6 studies that included 253 total patients and reported no significant differences in pulmonary function between devices.[4] Based on these findings, the ACCP/ACAAI group recommended both nebulizers and MDIs with spacers/holding chambers are appropriate for use in the inpatient setting. Quality of evidence: good.[4]

WHY USE MDIs FOR INPATIENTS

If MDI and nebulizer treatments are equally effective, why change current practice? The use of MDIs, rather than nebulizers, in hospitals could lead to fewer side effects such as tachycardia, arrhythmias, and tremors. MDIs are also more portable and do not require specialized set‐up. Furthermore, MDI administrations during hospitalization may provide a golden opportunity to have respiratory therapists, pharmacists, or other health professionals spend time teaching patients proper inhaler usage, rather than providing time‐consuming nebulizer treatments.[13] In a recent study, approximately 86% of hospitalized patients with asthma or COPD could not demonstrate appropriate use of an MDI. However, 100% of patients were able to achieve mastery following a short teach‐back session.[14] It is conceivable that transitioning patients to MDIs earlier during hospitalization and providing them with education regarding proper MDI administration could instill confidence in their use of inhalers and result in downstream effects such as shorter lengths of stay, less frequent hospital readmissions, or improved quality of life.

MDI use may result in cost savings in certain settings, although the relative costs of nebulizer versus MDI treatments depends on many institution‐specific factors. Such factors include the institutional policies on who delivers the nebulizer or the MDI and how they are compensated and staffed. For example in the Nebs No More After 24 program initiated at the University of California, San Francisco, the vast majority of the realized cost savings are due to the reduction in respiratory therapist time spent delivering MDIs, which reflects the local policies and compensation structure.[13] Previous inpatient interventions to convert from nebulizers to MDIs also showed cost savings resulting from decreased labor needs.[15] In some hospitals, nurses deliver nebulizer treatments, whereas in others only respiratory therapists are allowed to provide nebulizers. Moreover, whether the MDI can go home with the patient upon discharge depends on whether the hospital has a dispensing pharmacy or not. Formal economic evaluations specific to the local institution are necessary.

WHAT WE SHOULD DO INSTEAD: ENCOURAGE THE USE OF MDIs FOR INPATIENTS

For effective inpatient MDI treatments, MDI technique must be good. Thus, it is vital to enlist the right people to provide proper MDI teaching and supervision. Respiratory therapists are generally trained for this task, and may be complemented by appropriately trained physicians, nurses, or pharmacists. Many institutions have successfully implemented respiratory therapist‐driven protocols for the administration of MDIs, which has led to measurable improvements in the utilization of appropriate respiratory care resources.[15, 16] At University of California, San Francisco, this was accomplished by recruiting respiratory therapists and nurses to help support the transition of patients from nebulizers to MDIs and to provide bedside teaching on proper MDI usage. The institution then launched a Nebs No More After 24 campaign that sought to transition patients from nebulizers to MDIs within 24 hours of hospitalization. This campaign included an educational program for physicians, prepared facilitator guides to assist attending physicians with teaching about the new initiative, publicity efforts including pens and strategically placed posters, and regular feedback regarding nebulizer utilization on the pilot ward. Although the evidence suggests that patients can be started on MDIs immediately upon presentation to the ED, the UCSF campaign focused on transitioning patients within 24 hours so to alleviate concerns about transitions in care between the ED and the medical ward, as well as between overnight and day teams. MDIs are only as or more effective than nebulizers if the correct administration technique is employed. The 24‐hour transition period allows for MDI teaching and transition during regular daytime hours.

Inpatient use of nebulizers may be more appropriate than MDIs for patients with dementia or altered mental status, as well as those in extreme distress resulting in an inability to coordinate inhaler usage. Very low health literacy may be an additional barrier to appropriate MDI teaching and usage.

RECOMMENDATIONS

In patients with obstructive pulmonary symptoms, transition patients from nebulizers to MDIs early in their hospital course, unless the patient is unable to use an inhaler due to altered mental status, dementia, or other circumstances. Ensure that patients are instructed and supervised on proper MDI technique. Enlisting respiratory therapists and appropriately trained staff (pharmacists, nurses, physicians) is key to the successful use of MDIs. Frequency and dosage of MDIs used should be comparable to that of nebulized treatments. Although studies have used a relatively wide range of albuterol MDI dosing, prior programs have determined a dose of albuterol 4 puffs via MDI as being equivalent to the standard albuterol 2.5 mg nebulizer dosage.[17, 18] Some studies have advocated for using a range of 2 to 10 puffs albuterol MDI, with the actual dose based on clinical response.[17] One study in children with mild acute asthma found that 2 puffs of albuterol by MDI was just as effective as higher doses delivered by MDI (610 puffs) or by nebulizer.[19]

CONCLUSION

MDIs with holding chambers are clinically equivalent to nebulizer therapy for the treatment of both children and adults with obstructive pulmonary symptoms, as long as MDI technique and MDI dosing is adequate. This is based on good data in the ED setting but fewer studies in adult inpatients. There are a number of advantages to the use of inpatient MDIs over nebulizers; MDIs are more portable, often less expensive to use, may result in fewer side effects, and will hopefully improve outpatient MDI technique. The delivery of MDIs during hospitalization should be accompanied with patient education regarding proper administration technique.

Disclosure

Nothing to report.

Do you think this is a low‐value practice? Is this truly a Thing We Do for No Reason? Share what you do in your practice and join in the conversation online by retweeting it on Twitter (#TWDFNR) and Liking It on Facebook. We invite you to propose ideas for other Things We Do for No Reason topics by emailing [email protected]

The Things We Do for No Reason (TWDFNR) series reviews practices which have become common parts of hospital care but which may provide little value to our patients. Practices reviewed in the TWDFNR series do not represent black and white conclusions or clinical practice standards, but are meant as a starting place for research and active discussions among hospitalists and patients. We invite you to be part of that discussion. https://www.choosingwisely.org/

CASE PRESENTATION

A 54‐year‐old woman presented to the emergency department (ED) with shortness of breath. She reported that her primary care physician diagnosed her with chronic obstructive pulmonary disease (COPD). Her physician had prescribed her an albuterol inhaler to use as needed for shortness of breath. Over the past few weeks she had been trying to use the inhaler, but she noted that it did not seem to help her increasing wheezing, coughing, and sputum production. In the ED, she received continuous albuterol treatments via nebulizer, Solu‐Medrol 125 mg intravenously, antibiotics, and a chest x‐ray. She was admitted to the hospital medicine service for COPD exacerbation and started on nebulized bronchodilator treatments every 4 hours. By the fourth day of her hospital stay, she was discharged to home with an albuterol inhaler, oral prednisone, oral doxycycline, and a follow‐up appointment. Dedicated patient education regarding proper inhaler administration did not occur during hospitalization.

WHY YOU MIGHT THINK NEBULIZED TREATMENTS IN INPATIENTS ARE HELPFUL

Inhaled bronchodilators are a mainstay of therapy for acute obstructive pulmonary diseases, including COPD and asthma exacerbations.[1, 2] Inhaled bronchodilators may be delivered by metered‐dose inhalers (MDIs) or via wet nebulizers powered by compressed air or oxygen. Current practice patterns in EDs and hospital wards tend to favor the use of nebulizers due to many apparent advantages of these devices.[3] For instance, nebulizers do not require any special inhalation technique and can be effectively used by patients at any age.[3, 4] There is also a common perception that nebulizers are more effective, possibly stemming from the assumption that hospitalized patients have already failed their outpatient MDI therapy and an almost mystical belief in the healing power of mist. Moreover, many clinicians have been trained to routinely use nebulizer therapies and may lack sufficient knowledge or comfort about the relative efficacy and equivalence dosing of MDI therapies.

WHY NEBULIZERS ARE NOT BETTER THAN MDIs FOR PATIENTS HOSPITALIZED WITH OBSTRUCTIVE PULMONARY SYMPTOMS

Decades of research support that MDIs are effective, efficient, and less costly (depending on circumstances) than nebulizers for the routine treatment of obstructive pulmonary exacerbations.[3, 4, 5, 6, 7, 8, 9, 10, 11] The clinical effectiveness of MDIs has been shown in studies across populations of adults with acute COPD symptoms,[3, 4, 7, 8] as well as children and adults with asthma exacerbations.[3, 4, 5, 6, 9, 10] A 2005 joint report by the American College of Chest Physicians (ACCP) and the American College of Asthma, Allergy and Immunology (ACAAI), concluded none of the pooled meta‐analyses showed a significant difference between devices in any efficacy outcome in any patient group for each of the clinical settings.[4] Many different outcomes have been investigated, including forced expiratory volumes (FEV), peak flows, symptoms and specific symptom scores, and physical findings.[4]

Compared to MDIs, there are a number of drawbacks to the use of nebulizers: nebulizers are more expensive to buy and maintain, are less portable, and take longer to set up, use, and clean following each use.[12] In addition, nebulizers have been associated with greater increases in heart rate and tremors compared to MDIs, suggesting nebulizers lead to higher systemically absorbed ‐agonist doses.[4]

Of note, nearly all of the clinical effectiveness studies administered MDIs with a valved holding chamber or spacer, facilitating the delivery of drug to the airways.[3, 4] Although valved holding chambers are commonly referred to as a spacer, a true spacer does not have a valve and is rarely used today.[12]

THE EVIDENCE EXAMINING NEBULIZERS VERSUS MDIs IN PATIENTS WITH ASTHMA OR COPD EXACERBATIONS

A 2013 Cochrane review sought to establish the relative efficacy of MDIs with holding chambers versus nebulizers for children and adults who presented to a community setting or emergency department with acute asthma.[6] The review included a total of 1897 children and 729 adults in 39 randomized controlled trials. The authors judged the overall evidence to be of moderate quality. Children with acute asthma treated with MDIs in the ED had shorter lengths of stay in the ED (70 minutes vs 103 minutes), similar peak flow and FEV measurements, lower heart rates, and less tremor compared to children treated with nebulizers.[5, 6] There were no significant differences found between devices for the treatment of adult patients with asthma.[6]

In a separate double‐blind, randomized, placebo‐controlled study evaluating albuterol administered by nebulizer versus MDI with spacer for children <2 years old presenting to an ED with wheezing, the use of MDIs with a spacer and facemask was equally efficacious and may have led to fewer hospital admissions.[10]

Mandelberg et al. performed a double‐blind, randomized, placebo‐controlled trial for unselected adult patients presenting to an ED with obstructive pulmonary symptoms.[8] Patients received either 2 puffs of a placebo MDI with a spacer along with nebulized salbutamol 0.5 mL in 1.5 mL saline solution (n=25), or a salbutamol MDI along with a nebulized placebo saline solution (n=25). Treatments were repeated every 15 minutes up to 3 times, unless side effects occurred. Spirometric measurements were performed following each treatment. No differences were seen between the groups at any point during the study period. The authors concluded, Even in the setting of the unselected group of patient referrals to the [Department of Emergency Medicine] for episodes of severe airflow limitation, the clinical and objective bronchodilator responses to the administration of salbutamol are independent of the method of delivery: MDI with large spacer or aerosol nebulization.[8]

There are surprisingly few studies examining the use of nebulizers versus MDIs in the inpatient setting for both children and adults. Dolovich et al. reviewed 6 studies that included 253 total patients and reported no significant differences in pulmonary function between devices.[4] Based on these findings, the ACCP/ACAAI group recommended both nebulizers and MDIs with spacers/holding chambers are appropriate for use in the inpatient setting. Quality of evidence: good.[4]

WHY USE MDIs FOR INPATIENTS

If MDI and nebulizer treatments are equally effective, why change current practice? The use of MDIs, rather than nebulizers, in hospitals could lead to fewer side effects such as tachycardia, arrhythmias, and tremors. MDIs are also more portable and do not require specialized set‐up. Furthermore, MDI administrations during hospitalization may provide a golden opportunity to have respiratory therapists, pharmacists, or other health professionals spend time teaching patients proper inhaler usage, rather than providing time‐consuming nebulizer treatments.[13] In a recent study, approximately 86% of hospitalized patients with asthma or COPD could not demonstrate appropriate use of an MDI. However, 100% of patients were able to achieve mastery following a short teach‐back session.[14] It is conceivable that transitioning patients to MDIs earlier during hospitalization and providing them with education regarding proper MDI administration could instill confidence in their use of inhalers and result in downstream effects such as shorter lengths of stay, less frequent hospital readmissions, or improved quality of life.

MDI use may result in cost savings in certain settings, although the relative costs of nebulizer versus MDI treatments depends on many institution‐specific factors. Such factors include the institutional policies on who delivers the nebulizer or the MDI and how they are compensated and staffed. For example in the Nebs No More After 24 program initiated at the University of California, San Francisco, the vast majority of the realized cost savings are due to the reduction in respiratory therapist time spent delivering MDIs, which reflects the local policies and compensation structure.[13] Previous inpatient interventions to convert from nebulizers to MDIs also showed cost savings resulting from decreased labor needs.[15] In some hospitals, nurses deliver nebulizer treatments, whereas in others only respiratory therapists are allowed to provide nebulizers. Moreover, whether the MDI can go home with the patient upon discharge depends on whether the hospital has a dispensing pharmacy or not. Formal economic evaluations specific to the local institution are necessary.

WHAT WE SHOULD DO INSTEAD: ENCOURAGE THE USE OF MDIs FOR INPATIENTS

For effective inpatient MDI treatments, MDI technique must be good. Thus, it is vital to enlist the right people to provide proper MDI teaching and supervision. Respiratory therapists are generally trained for this task, and may be complemented by appropriately trained physicians, nurses, or pharmacists. Many institutions have successfully implemented respiratory therapist‐driven protocols for the administration of MDIs, which has led to measurable improvements in the utilization of appropriate respiratory care resources.[15, 16] At University of California, San Francisco, this was accomplished by recruiting respiratory therapists and nurses to help support the transition of patients from nebulizers to MDIs and to provide bedside teaching on proper MDI usage. The institution then launched a Nebs No More After 24 campaign that sought to transition patients from nebulizers to MDIs within 24 hours of hospitalization. This campaign included an educational program for physicians, prepared facilitator guides to assist attending physicians with teaching about the new initiative, publicity efforts including pens and strategically placed posters, and regular feedback regarding nebulizer utilization on the pilot ward. Although the evidence suggests that patients can be started on MDIs immediately upon presentation to the ED, the UCSF campaign focused on transitioning patients within 24 hours so to alleviate concerns about transitions in care between the ED and the medical ward, as well as between overnight and day teams. MDIs are only as or more effective than nebulizers if the correct administration technique is employed. The 24‐hour transition period allows for MDI teaching and transition during regular daytime hours.

Inpatient use of nebulizers may be more appropriate than MDIs for patients with dementia or altered mental status, as well as those in extreme distress resulting in an inability to coordinate inhaler usage. Very low health literacy may be an additional barrier to appropriate MDI teaching and usage.

RECOMMENDATIONS

In patients with obstructive pulmonary symptoms, transition patients from nebulizers to MDIs early in their hospital course, unless the patient is unable to use an inhaler due to altered mental status, dementia, or other circumstances. Ensure that patients are instructed and supervised on proper MDI technique. Enlisting respiratory therapists and appropriately trained staff (pharmacists, nurses, physicians) is key to the successful use of MDIs. Frequency and dosage of MDIs used should be comparable to that of nebulized treatments. Although studies have used a relatively wide range of albuterol MDI dosing, prior programs have determined a dose of albuterol 4 puffs via MDI as being equivalent to the standard albuterol 2.5 mg nebulizer dosage.[17, 18] Some studies have advocated for using a range of 2 to 10 puffs albuterol MDI, with the actual dose based on clinical response.[17] One study in children with mild acute asthma found that 2 puffs of albuterol by MDI was just as effective as higher doses delivered by MDI (610 puffs) or by nebulizer.[19]

CONCLUSION

MDIs with holding chambers are clinically equivalent to nebulizer therapy for the treatment of both children and adults with obstructive pulmonary symptoms, as long as MDI technique and MDI dosing is adequate. This is based on good data in the ED setting but fewer studies in adult inpatients. There are a number of advantages to the use of inpatient MDIs over nebulizers; MDIs are more portable, often less expensive to use, may result in fewer side effects, and will hopefully improve outpatient MDI technique. The delivery of MDIs during hospitalization should be accompanied with patient education regarding proper administration technique.

Disclosure

Nothing to report.

Do you think this is a low‐value practice? Is this truly a Thing We Do for No Reason? Share what you do in your practice and join in the conversation online by retweeting it on Twitter (#TWDFNR) and Liking It on Facebook. We invite you to propose ideas for other Things We Do for No Reason topics by emailing [email protected]

References
  1. Global Initiative for Chronic Obstructive Lung Disease (GOLD). Global strategy for the diagnosis, management, and prevention of COPD. Available at: http://www.goldcopd.org/guidelines‐global‐strategy‐for‐diagnosis‐management.html. Updated January 2015. Accessed September 25, 2014.
  2. National Heart Lung and Blood Institute. National Asthma Education and Prevention Program. Expert panel report 3: guidelines for the diagnosis and management of asthma. Available at: http://www.nhlbi.nih.gov/guidelines/asthma/asthgdln.htm. Published 2007. Updated April 2012. Accessed September 25, 2014.
  3. Turner MO, Patel A, Ginsburg S, FitzGerald JM. Bronchodilator delivery in acute airflow obstruction. A meta‐analysis. Arch Intern Med. 1997;157(15):17361744.
  4. Dolovich MB, Ahrens RC, Hess DR, et al. Device selection and outcomes of aerosol therapy: Evidence‐based guidelines: American College of Chest Physicians/American College of Asthma, Allergy, and Immunology. Chest. 2005;127(1):335371.
  5. Castro‐Rodriguez JA, Rodrigo GJ. Beta‐agonists through metered‐dose inhaler with valved holding chamber versus nebulizer for acute exacerbation of wheezing or asthma in children under 5 years of age: a systematic review with meta‐analysis. J Pediatr. 2004;145(2):172177.
  6. Cates CJ, Welsh EJ, Rowe BH. Holding chambers (spacers) versus nebulisers for beta‐agonist treatment of acute asthma. Cochrane Database Syst Rev. 2013;9:CD000052.
  7. Berry RB, Shinto RA, Wong FH, Despars JA, Light RW. Nebulizer vs spacer for bronchodilator delivery in patients hospitalized for acute exacerbations of COPD. Chest. 1989;96(6):12411246.
  8. Mandelberg A, Chen E, Noviski N, Priel IE. Nebulized wet aerosol treatment in emergency department—is it essential? Comparison with large spacer device for metered‐dose inhaler. Chest. 1997;112(6):15011505.
  9. Deerojanawong J, Manuyakorn W, Prapphal N, Harnruthakorn C, Sritippayawan S, Samransamruajkit R. Randomized controlled trial of salbutamol aerosol therapy via metered dose inhaler‐spacer vs. jet nebulizer in young children with wheezing. Pediatr Pulmonol. 2005;39(5):466472.
  10. Delgado A, Chou KJ, Silver EJ, Crain EF. Nebulizers vs metered‐dose inhalers with spacers for bronchodilator therapy to treat wheezing in children aged 2 to 24 months in a pediatric emergency department. Arch Pediatr Adolesc Med. 2003;157(1):7680.
  11. Turner MO, Gafni A, Swan D, FitzGerald JM. A review and economic evaluation of bronchodilator delivery methods in hospitalized patients. Arch Intern Med. 1996;156(18):21132118.
  12. Rottier BL, Rubin BK. Asthma medication delivery: mists and myths. Paediatr Respir Rev. 2013;14(2):112118.
  13. Moriates C, Novelero M, Quinn K, Khanna R, Mourad M. “Nebs no more after 24”: a pilot program to improve the use of appropriate respiratory therapies. JAMA Intern Med. 2013;173(17):16471648.
  14. Press VG, Arora VM, Shah LM, et al. Misuse of respiratory inhalers in hospitalized patients with asthma or COPD. J Gen Intern Med. 2011;26(6):635642.
  15. Tenholder MF, Bryson MJ, Whitlock WL. A model for conversion from small volume nebulizer to metered dose inhaler aerosol therapy. Chest. 1992;101(3):634637.
  16. Kallam A, Meyerink K, Modrykamien AM. Physician‐ordered aerosol therapy versus respiratory therapist‐driven aerosol protocol: the effect on resource utilization. Respir Care. 2013;58(3):431437.
  17. Hendeles L, Hatton RC, Coons TJ, Carlson L. Automatic replacement of albuterol nebulizer therapy by metered‐dose inhaler and valved holding chamber. Am J Health Syst Pharm. 2005;62(10):10531061.
  18. Salyer JW, DiBlasi RM, Crotwell DN, Cowan CA, Carter ER. The conversion to metered‐dose inhaler with valved holding chamber to administer inhaled albuterol: a pediatric hospital experience. Respir Care. 2008;53(3):338345.
  19. Schuh S, Johnson DW, Stephens D, Callahan S, Winders P, Canny GJ. Comparison of albuterol delivered by a metered dose inhaler with spacer versus a nebulizer in children with mild acute asthma. J Pediatr. 1999;135(1):2227.
References
  1. Global Initiative for Chronic Obstructive Lung Disease (GOLD). Global strategy for the diagnosis, management, and prevention of COPD. Available at: http://www.goldcopd.org/guidelines‐global‐strategy‐for‐diagnosis‐management.html. Updated January 2015. Accessed September 25, 2014.
  2. National Heart Lung and Blood Institute. National Asthma Education and Prevention Program. Expert panel report 3: guidelines for the diagnosis and management of asthma. Available at: http://www.nhlbi.nih.gov/guidelines/asthma/asthgdln.htm. Published 2007. Updated April 2012. Accessed September 25, 2014.
  3. Turner MO, Patel A, Ginsburg S, FitzGerald JM. Bronchodilator delivery in acute airflow obstruction. A meta‐analysis. Arch Intern Med. 1997;157(15):17361744.
  4. Dolovich MB, Ahrens RC, Hess DR, et al. Device selection and outcomes of aerosol therapy: Evidence‐based guidelines: American College of Chest Physicians/American College of Asthma, Allergy, and Immunology. Chest. 2005;127(1):335371.
  5. Castro‐Rodriguez JA, Rodrigo GJ. Beta‐agonists through metered‐dose inhaler with valved holding chamber versus nebulizer for acute exacerbation of wheezing or asthma in children under 5 years of age: a systematic review with meta‐analysis. J Pediatr. 2004;145(2):172177.
  6. Cates CJ, Welsh EJ, Rowe BH. Holding chambers (spacers) versus nebulisers for beta‐agonist treatment of acute asthma. Cochrane Database Syst Rev. 2013;9:CD000052.
  7. Berry RB, Shinto RA, Wong FH, Despars JA, Light RW. Nebulizer vs spacer for bronchodilator delivery in patients hospitalized for acute exacerbations of COPD. Chest. 1989;96(6):12411246.
  8. Mandelberg A, Chen E, Noviski N, Priel IE. Nebulized wet aerosol treatment in emergency department—is it essential? Comparison with large spacer device for metered‐dose inhaler. Chest. 1997;112(6):15011505.
  9. Deerojanawong J, Manuyakorn W, Prapphal N, Harnruthakorn C, Sritippayawan S, Samransamruajkit R. Randomized controlled trial of salbutamol aerosol therapy via metered dose inhaler‐spacer vs. jet nebulizer in young children with wheezing. Pediatr Pulmonol. 2005;39(5):466472.
  10. Delgado A, Chou KJ, Silver EJ, Crain EF. Nebulizers vs metered‐dose inhalers with spacers for bronchodilator therapy to treat wheezing in children aged 2 to 24 months in a pediatric emergency department. Arch Pediatr Adolesc Med. 2003;157(1):7680.
  11. Turner MO, Gafni A, Swan D, FitzGerald JM. A review and economic evaluation of bronchodilator delivery methods in hospitalized patients. Arch Intern Med. 1996;156(18):21132118.
  12. Rottier BL, Rubin BK. Asthma medication delivery: mists and myths. Paediatr Respir Rev. 2013;14(2):112118.
  13. Moriates C, Novelero M, Quinn K, Khanna R, Mourad M. “Nebs no more after 24”: a pilot program to improve the use of appropriate respiratory therapies. JAMA Intern Med. 2013;173(17):16471648.
  14. Press VG, Arora VM, Shah LM, et al. Misuse of respiratory inhalers in hospitalized patients with asthma or COPD. J Gen Intern Med. 2011;26(6):635642.
  15. Tenholder MF, Bryson MJ, Whitlock WL. A model for conversion from small volume nebulizer to metered dose inhaler aerosol therapy. Chest. 1992;101(3):634637.
  16. Kallam A, Meyerink K, Modrykamien AM. Physician‐ordered aerosol therapy versus respiratory therapist‐driven aerosol protocol: the effect on resource utilization. Respir Care. 2013;58(3):431437.
  17. Hendeles L, Hatton RC, Coons TJ, Carlson L. Automatic replacement of albuterol nebulizer therapy by metered‐dose inhaler and valved holding chamber. Am J Health Syst Pharm. 2005;62(10):10531061.
  18. Salyer JW, DiBlasi RM, Crotwell DN, Cowan CA, Carter ER. The conversion to metered‐dose inhaler with valved holding chamber to administer inhaled albuterol: a pediatric hospital experience. Respir Care. 2008;53(3):338345.
  19. Schuh S, Johnson DW, Stephens D, Callahan S, Winders P, Canny GJ. Comparison of albuterol delivered by a metered dose inhaler with spacer versus a nebulizer in children with mild acute asthma. J Pediatr. 1999;135(1):2227.
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Nebulized bronchodilators instead of metered‐dose inhalers for obstructive pulmonary symptoms
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Nebulized bronchodilators instead of metered‐dose inhalers for obstructive pulmonary symptoms
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Address for correspondence and reprint requests: Christopher Moriates, MD, University of California at San Francisco, 505 Parnassus Ave., M1287, San Francisco, CA 94143‐0131; Telephone: 415‐476‐9852; Fax: 415‐502‐1963; E‐mail: [email protected]
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Variation in Readmission Rates by EDs

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Variation in readmission rates by emergency departments and emergency department providers caring for patients after discharge

Readmissions of Medicare beneficiaries within 30 days of discharge are frequent and costly.[1] Concern about readmissions has prompted the Centers for Medicare & Medicaid Services (CMS) to reduce payments to hospitals with excess readmissions.[2] Research has identified a number of patient clinical and socio‐demographic factors associated with readmissions.[3] However, interventions designed to reduce readmissions have met with limited success. In a systematic review, no single intervention was regularly effective in reducing readmissions, despite the fact that interventions have targeted both predischarge, transition of care, and postdischarge processes of care.[4]

The different trajectories of care experienced by patients after hospital discharge, and their effect on risk of readmission, have been incompletely studied. Although early outpatient follow‐up after discharge is associated with lower readmission rates,[5, 6] a factor that has been minimally studied is the role of the emergency department (ED) and the ED provider in readmissions. The ED and ED providers feature prominently in the care received by patients shortly after discharge from a hospital. About a quarter of all hospitalized Medicare patients are evaluated in an ED within 30 days of discharge,[7, 8] and a majority of readmissions within 30 days of discharge are precipitated by an ED visit.[9] Hence, we asked whether when a recently discharged patient is seen in an ED, does the rate of readmission vary by ED provider and by ED facility?

We used Texas Medicare claims data to examine patients visiting the ED within 30 days of discharge from an initial hospitalization to determine if their risk of readmission varies by the ED provider caring for them and by the ED facility they visit.

METHODS

Sources of Data

We used claims from the years 2007 to 2011 for 100% of Texas Medicare beneficiaries, including Medicare beneficiary summary files, Medicare Provider Analysis and Review (MedPAR) files, Outpatient Standard Analytical Files (OutSAF), and Medicare Carrier files. We obtained diagnosis‐related group associated information, including weights, and Major Diagnostic Category from CMS, and used Provider of Services files to determine facility characteristics.

Establishment of the Study Cohort

From 2008 through 2011 MedPAR files, we initially selected all hospital discharges from acute‐care hospitals in Texas. From these 3,191,160 admissions, we excluded those discharged dead or transferred to other acute‐care hospitals (N=230,343), those who were younger than 66 years at admission (N=736,685) and those without complete Parts A and B enrollment or with any health maintenance organization enrollment in the 12 months prior to and 2 months after the admission of interest (N=596,427). From the remaining 1,627,705 discharges, we identified 302,949 discharges that were followed by at least 1 ED visit within 30 days.

We applied the algorithm developed by Kaskie et al. to identify ED visits.[10] We identified claims for ED services with Current Procedural Terminology (CPT) codes 99281‐99285 from Carrier files and bundled claims with overlapping dates or those that were within 1 day of each other. Then we identified claims for ED services using the same CPT codes from OutSAF and bundled those with overlapping dates or those that were within 3 days of each other. Finally, we bundled Carrier and OutSAF claims with overlapping dates and defined them as the same ED visit. From these, we retained only the first ED visit. We excluded those receiving care from multiple ED providers during the ED visit (N=38,565), and those who had a readmission before the first ED visit (N=1436), leaving 262,948 ED visits. For patients who had more than 1 hospitalization followed by an ED visit in a given year, we selected the first hospitalization, resulting in 199,143 ED visits. We then selected ED providers associated with at least 30 ED visits in this cohort, resulting in 1922 ED providers and 174,209 ED visits. For analyses where we examined both ED provider and facility variation in admission rates, we eliminated ED providers that generated charges from more than 1 ED facility, resulting in 525 providers and 48,883 ED visits at 143 ED facilities.

Measures

Patient Characteristics

We categorized beneficiaries by age, gender, and ethnicity using Medicare beneficiary summary files. We used the Medicaid indicator as a proxy of low socioeconomic status. We obtained information on weekend admission, emergent admission, discharge destination, and diagnosis‐related groupt (DRG) from MedPAR files. We identified comorbidities using the claims from MedPAR, Carrier, and OutSAF files in the year prior to the admission.[11] We identified total hospitalizations and outpatient visits in the prior year from MedPAR files and Carrier files, respectively. We obtained education status at the level of zip code of residence from the 2011 American Community Survey estimates from the United States Census Bureau. We determined urban or rural residence using the 2013 Rural‐Urban Continuum Codes developed by the United States Department of Agriculture.

ED Facility Characteristics

We used the provider number of the ED facility to link to the Provider of Services files and obtained information on medical school affiliation, facility size, and for profit status.

Study Outcomes

The outcome of this study was readmission after an ED visit within 30 days of discharge from an initial hospitalization. We defined readmission after an ED visit as a hospitalization starting the day of or the day following the ED visit

Statistical Analyses

We performed 2‐level analyses where patients were clustered with ED providers to examine variation among ED providers. The effect of ED providers was modeled as a random effect to account for the correlation among the patients cared for by the same ED provider. We derived ED provider‐specific estimates from models adjusted for patient age, gender, race/ethnicity, rural or urban residence, Medicaid eligibility, education at the zip code level of residence, and characteristics of the initial admission (emergency admission, weekend admission, discharge destination, its major diagnostic category and DRG weight). We also adjusted for comorbidities, number of hospitalizations, and number of physician visits in the year before the initial admission.

We also conducted 2‐level analyses where patients were nested in ED facilities and 3‐level analyses where patients were nested in ED providers and ED providers were nested in ED facilities. We adjusted for all factors described above. We computed the change in the variance between 2‐level and 2‐level analyses to determine the variation in readmission rates that was explained by the ED provider and the ED facility. All analyses were performed with SAS version 9.2 (SAS Institute Inc., Cary, NC).

RESULTS

We identified 174,209 patients who visited an ED within 30 days of discharge from an initial hospitalization. Table 1 describes the characteristics of these patients as well as the readmission rates associated with these characteristics. The rate of readmission of our cohort of 1,627,705 discharges with or without a following ED visit was 16.2%, whereas the rate of readmission following an ED visit in our final cohort of 174,209 patients was 52.67%. This readmission rate increased with age, from 49.31% for patients between 66 and 70 years of age to 55.33% for patients older than 85 years. There were minor variations by gender and ethnicity. Patients residing in metropolitan areas or in zip codes with low education levels had higher readmission rates, as did those whose original admission was classified as emergency or those who were not discharged home.

The Effect of Patient Characteristics on the Risk of Hospitalization During an ED Visit Within 30 Days of Hospital Discharge
Patient CharacteristicNo. of ED Visits (%)% ReadmittedOdds Ratio (95% CI)a
 MeanSD, Median (Q1Q3)Odds Ratio (95% CI)a
  • NOTE: There were 141 patients with unknown education level and 22 with unknown place (rural/urban) of residence. These were included as a separate category in the analyses but are not shown. Abbreviations: CI, confidence interval; DGR, diagnosis‐related group; ED, emergency department; SD, standard deviation.

  • Estimated from 2‐level models adjusted for other patient characteristics.

  • Statistically significant results.

  • Percent of persons age 25+ years with high school education or higher at the zip code of residence.

Overall174,209 (100)52.67 
Age, y   
667032,962 (18.92)49.311.00
717534,979 (20.08)51.481.10 (1.06‐1.13)b
768036,728 (21.08)53.011.15 (1.12‐1.19)b
818534,784 (19.97)54.051.19 (1.15‐1.23)b
>8534,756 (19.95)55.331.25 (1.21‐1.29)b
Gender   
Male71,049 (40.78)52.951.02 (1.00‐1.04)
Female103,160 (59.22)52.481.00
Race   
Non‐Hispanic white124,312 (71.36)52.771.00
Black16,809 (9.65)51.450.84 (0.81‐0.87)b
Hispanic30,618 (17.58)52.700.88 (0.85‐0.91)b
Other2,470 (1.42)55.711.06 (0.97‐1.15)
Rural/urban residence   
Metropolitan136,739 (78.49)53.881.00
Nonmetropolitan35,000 (20.09)48.160.96 (0.93‐0.99)b
Rural2,448 (1.41)50.041.04 (0.95‐1.13)
Medicaid eligible   
No128,909 (74.00)52.651.00
Yes45,300 (26.00)52.720.97 (0.94‐0.99)b
Education levelc   
1st quartile (lowest)43,863 (25.18)54.611.00
2nd quartile43,316 (24.86)53.921.00 (0.97‐1.03)
3rd quartile43,571 (25.01)50.720.99 (0.96‐1.02)
4th quartile (highest)43,318 (24.87)51.981.01 (0.97‐1.04)
Emergency admission   
No99,101 (56.89)51.151.00
Yes75,108 (43.11)54.681.07 (1.05‐1.09)b
Weekend admission   
No131,266 (75.35)52.451.00
Yes42,943 (24.65)53.351.01 (0.99‐1.04)
Discharge destination   
Home122,542 (70.34)50.901.00
Inpatient rehabilitation facility9,512 (5.46)55.481.31 (1.25‐1.37)b
Skilled nursing facility37,248 (21.38)57.251.29 (1.26‐1.33)b
Other4,907 (2.82)56.881.14 (1.07‐1.21)b
DRG weight (per unit)1.561.27, 0.82 (1.16‐1.83)1.06 (1.05‐1.07)b
Hospitalization in the prior year (per hospitalization)1.031.49, 0.00 (1.00‐2.00)1.04 (1.03‐1.04)b
Physician visits in the prior year (per 10 visits)11.759.80, 5.00 (10.00‐17.00)0.97 (0.96‐0.98)b

Table 1 also presents the odds of readmission adjusted for all other factors in the table and also adjusted for clustering within ED providers in a 2‐level model. Increasing age, white race, metropolitan residence, nonhome discharge, higher severity of illness, more hospitalizations in the prior year, fewer physician visits in the prior year, and an emergency initial admission were each associated with a higher readmission rate.

We next generated estimates of readmission rates for each ED provider from the adjusted 2‐level models. Figure 1 shows the adjusted cumulative readmission rates for the 1922 ED providers. This figure shows the mean value and 95% confidence intervals of the readmission rates for each provider. Dark vertical lines indicate providers whose readmission rate differed significantly from the mean adjusted readmission rate of 52.1% for all providers. Of the ED providers, 14.2% had significantly higher readmission rates. The mean readmission rate for these 272 providers was 67.2%. Of the ED providers, 14.7% had significantly lower readmission rates. The mean readmission rate for these 283 providers was 36.8%.

Figure 1
Ranking of emergency department (ED) provider by adjusted readmission rate: readmission on the day of or day after ED visit. Rates were estimated by 2‐level analyses, adjusted for patient characteristics. The horizontal line represents the overall mean. Error bars represent 95% confidence intervals of the estimate for the individual ED provider. Black error bars represent ED providers with significantly higher or lower estimates.

To determine the contribution of the ED facility to the variation in readmission rates, we restricted our analysis to 48,883 patients (28.06% of our cohort) seen by 525 ED providers who were associated with only 1 facility (total of 143 facilities). Table 2 describes the unadjusted readmission rates stratified by specific characteristics of those facilities. The unadjusted readmission rate increased with the size of the associated hospital, from 47.61% for hospitals with less than 100 beds to 57.06% for hospitals with more than 400 beds. The readmission rate for nonprofit facilities was 53.81% and for for‐profit facilities was 57.39%. Facilities with no medical school affiliation had a readmission rate of 54.51%, whereas those with a major affiliation had a readmission rate of 58.72%.

The Effect of ED Facility Characteristics on the Risk of Readmission After an ED Visit
ED Facility CharacteristicNo. of ED Visits (%)% ReadmittedOdds Ratio (95% CI)a
  • NOTE: Abbreviations: CI, confidence interval; ED, emergency department.

  • Estimated from 3‐level models adjusted for patient characteristics. ED providers associated with only 1 hospital from 2008 through 2011 were selected for the 3‐level analyses. There were 525 ED providers from 143 facilities.

  • Statistically significant results.

Overall48,883  
Total beds   
1003,936 (8.05)47.611.00
1012006,251 (12.79)52.071.38 (1.06‐1.81)b
20140013,000 (26.59)56.261.69 (1.32‐2.17)b
>40025,696 (52.57)57.061.77 (1.35‐2.33)b
Type of control   
Nonprofit24,999 (51.14)53.811.00
Proprietary17,108 (35.00)57.391.32 (1.09‐1.61)b
Government6,776 (13.86)56.601.11 (0.88‐1.41)
Medical school affiliation   
Major6,487 (13.27)58.721.00
Limited7,066 (14.45)56.370.85 (0.58‐1.25)
Graduate3,164 (6.47)56.190.71 (0.44‐1.15)
No affiliation32,166 (65.80)54.510.78 (0.57‐1.05)
If the same hospital patient was discharged from   
Yes38,532 (78.82)55.640.96 (0.91‐1.00)
No10,351 (21.18)54.731.00

With this smaller cohort, we performed 2 types of 2‐level models, where patients clustered within ED facilities and ER providers, respectively, and a 3‐level model accounting for clustering of patients within providers and of providers within facilities. From the facility‐patient 2‐level model, the variance of the ED facility was 0.2718 (95% confidence interval [CI]: 0.2083‐0.3696). From the provider‐patient 2‐level model, the variance of ED provider was 0.2532 (95% CI: 0.2166‐0.3002). However, when the 3‐level model was performed, the variance of ED provider decreased to 0.0893 (95% CI: 0.0723‐0.1132) and the variance of ED facility dropped to 0.2316 (95% CI: 0.1704‐0.3331) . This indicates 65% of the variation among ED providers was explained by the ED facility, and in contrast, 15% of the variation among ED facilities was explained by ED providers.

Table 2 also shows the adjusted odds of readmission generated from the 3‐level model. Patients receiving care in ED facilities in hospitals with more beds and in for‐profit hospitals were at higher risk for readmission. It is possible that patients seen at the ED associated with the discharging hospital had a lower risk of readmission. This finding was close to being statistically significant (P=0.051).

We repeated all the above analyses using an outcome of readmission anytime between the ED visit and 30 days after discharge from the initial hospitalization (rather than readmission on the day of or after the ED visit). All analyses produced results similar to the results presented above. For example, Figure 2 shows the adjusted cumulative readmission rates for the 1922 ED providers using this outcome. Of the ED providers, 12.8% had higher and 12.5% had lower readmission rates as compared to the mean readmission rate for all ED providers. The Spearman correlation coefficient between the rank of ED providers in immediate readmission rate (Figure 1) and readmission rate within 30 days of hospital discharge (Figure 2) was 0.94 (P<0.001).

Figure 2
Ranking of emergency department (ED) provider by adjusted readmission rate: readmission after an ED visit but anytime within 30 days of discharge from initial hospitalization. Rates were estimated by 2‐level analyses, adjusted for patient characteristics. The horizontal line represents the overall mean. Error bars represent 95% confidence intervals of the estimate for the individual ED provider. Black error bars represent ED providers with significantly higher or lower estimates.

DISCUSSION

This study found substantial variation in readmission rates by ED provider, despite controlling for patient clinical and sociodemographic factors. In 3‐level models, the ED facility explained a substantial part of the variation by ED provider, with patients seen at larger facilities and for‐profit facilities having higher readmission rates.

Variation among ED facilities and ED providers in readmission rates has not previously been studied. There is literature on the variation in ED facility and ED provider admission rates. As readmissions are a subset of all admissions, this literature provides context to our findings. Abualenain et al. examined admission rates for 89 ED physicians for adult patients presenting with an acute medical or surgical complaint at 3 EDs in a health system.[12] After adjusting for patient and clinical characteristics, admission rates varied from 21% to 49% among physicians and from 27% to 41% among 3 facilities. Two other studies from single hospitals have found similar variation among providers.[13, 14] The reasons for the variation among ED providers presumably relate to subjective aspects of clinical assessment and the reluctance of providers to rely solely on objective scales, even when they are available.[14, 15] Variation in admission rates among different facilities may relate to clustering of providers with similar practice styles within facilities, lack of clinical guidelines for certain conditions, as well as differences among facilities in the socioeconomic status and access to primary care of their clientele.[12, 16, 17] For example, Pines et al. have shown that ED facility admission rates are higher in communities with fewer primary care physicians per capita and are influenced by the prevailing county level admission rates.[16] Capp et al. showed persistent variation in admission rates across hospitals, despite adjusting for clinical criteria such as vital signs, chief complaints, and severity of illness.[18]

Structural differences in ED facilities may also influence the decision to admit. We found that patients visiting ED facilities in hospitals with more beds had a higher readmission rate. ED facility systems of care such as observation units or protocols are associated with lower admission rates.[19, 20] Finally, certain hospitals may actively influence the admission practice patterns of their ED providers. We noted that patients seen at for‐profit ED facilities had a greater risk of readmission. A similar finding has been described by Pines et al., who noted higher admission rates at for‐profit facilities.[16] In an extreme example, a recent Justice Department lawsuit alleged that a for‐profit hospital chain used software systems and financial incentives to ED providers to increase admissions.[21]

It is possible that the providers with low readmission rates may have inappropriately released patients who truly should have been admitted. A signal that this occurred would be if these patients were readmitted in the days after the ED visits. We examined this possibility by additionally examining readmissions occurring anytime between the ED visit until 30 days after discharge from the initial hospitalization. The results were similar to when we only included readmissions that occurred immediately following the ED visit, with a very high correlation (r=0.94) between the ranking of the ED providers by readmission rates in both circumstances. This suggests that the decisions of the ED providers with low readmission rates to admit or release from the ED were likely appropriate.

Our research has limitations. We studied patients with fee‐for‐service Medicare in a single large state in the United States over a 4‐year period. Our findings may not be generalizable to younger patient populations, other regions with different sociodemographic patterns and healthcare systems, or other time periods. We could not control for many factors that may impact the risk of readmission but are not measured in Medicare databases (eg, clinical data such as vital signs, measures of quality of transition from discharging hospital, ED provider workload). To attribute care to a single ED provider, we excluded patients who were taken care of by multiple ED providers. These patients may have different needs from our study population (eg, more complex issues and longer stays in the ED) and may bias our results.

This study provides a new direction for research and quality improvement targeting readmissions. Research should extend beyond the discharge transition and examine the entire trajectory of posthospitalization care to better understand readmissions. Based directly on this study, research could investigate the practice patterns of ED providers and systems of care at ED facilities that affect readmissions rates. Such investigation could inform quality improvement efforts to standardize care for patients in the ED.

CMS policies hold hospitals accountable for readmissions of the patients they discharge, but do not address the admission process in the ED that leads to readmissions of recently discharged patients. Given the present study, and the fact that the proportion of all hospital admissions that occur through the ED has grown to 44%,[22] consideration of the role of the ED in public policy efforts to discourage unnecessary inpatient care may be appropriate.

In summary, this study shows that a recently discharged patient's chances of being readmitted depends partly on the ED provider who evaluates them and on the ED facility at which they seek care. ED provider practice patterns and ED facility systems of care may be a target for interventions aimed at decreasing readmission rates.

Disclosures

This research was supported by grants from the National Institutes of Health (AG033134 and K05CA134923) and from the Agency for Healthcare Research and Quality (R24H5022134). The authors report no conflicts of interest.

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References
  1. Jencks SF, Williams MV, Coleman EA. Rehospitalizations among patients in the Medicare Fee‐for‐Service Program. N Engl J Med. 2009;360:14181428.
  2. Centers for Medicare 306:16881698.
  3. Hansen LO, Young RS, Hinami K, Leung A, Williams MV. Interventions to reduce 30‐day rehospitalization: a systematic review. Ann Intern Med. 2011;155:520528.
  4. Sharma G, Kuo Y, Freeman JL, Zhang DD, Goodwin JS. Outpatient follow‐up visit and 30‐day emergency department visit and readmission in patients hospitalized for chronic obstructive pulmonary disease. Arch Intern Med. 2010;170:16641670.
  5. Hernandez AF, Greiner MA, Fonarow GC, et al. Relationship between early physician follow‐up and 30‐day readmission among Medicare beneficiaries hospitalized for heart failure. JAMA. 2010;303:17161722.
  6. Goodman DC, Fisher ES, Chang C. After hospitalization: a Dartmouth Atlas report on post‐acute care for Medicare beneficiaries. Dartmouth Atlas website. Available at: www.dartmouthatlas.org/downloads/reports/Post_discharge_events_092811.pdf. Accessed August 8, 2013.
  7. Rising KL, White LF, Fernandez WG, Boutwell AE. Emergency department visits after hospital discharge: a missing part of the equation. Ann Emerg Med. 2013;62:145150.
  8. Kocher KE, Nallamothu BK, Birkmeyer JD, Dimick JB. Emergency department visits after surgery are common for Medicare patients, suggesting opportunities to improve care. Health Aff (Millwood). 2013;32:16001607.
  9. Kaskie B, Obrizan M, Cook E, et al. Defining emergency department episodes by severity and intensity: a 15‐year study of Medicare beneficiaries. BMC Health Serv Res. 2010;10:113.
  10. Elixhauser A, Steiner C, Harris DR, Coffey RM. Comorbidity measures for use with administrative data. Med Care. 1998;36:827.
  11. Abualenain J, Frohna WJ, Shesser R, Ding R, Smith M, Pines JM. Emergency department physician‐level and hospital‐level variation in admission rates. Ann Emerg Med. 2013;61:638643.
  12. Dean NC, Jones JP, Aronsky D, et al. Hospital admission decision for patients with community‐acquired pneumonia: variability among physicians in an emergency department. Ann Emerg Med. 2012;59:3541.
  13. Mutrie D, Bailey SK, Malik S. Individual emergency physician admission rates: predictably unpredictable. CJEM. 2009;11(2):149155.
  14. Aujesky D, McCausland JB, Whittle J, Obrosky DS, Yealy DM, Fine MJ. Reasons why emergency department providers do not rely on the pneumonia severity index to determine the initial site of treatment for patients with pneumonia. Clin Infect Dis. 2009;49:e100e108.
  15. Pines JM, Mutter RL, Zocchi MS. Variation in emergency department admission rates across the United States. Med Care Res Rev. 2013;70:218231.
  16. Venkatesh AK, Dai Y, Ross JS, Schuur JD, Capp R, Krumholz HM. Variation in US hospital emergency department admission rates by clinical condition. Med Care. 2015;53:237244.
  17. Capp R, Ross JS, Fox JP, et al. Hospital variation in risk‐standardized hospital admission rates from US EDs among adults. Am J Emerg Med. 2014;32:837843.
  18. Schrock JW, Reznikova S, Weller S. The effect of an observation unit on the rate of ED admission and discharge for pyelonephritis. Am J Emerg Med. 2010;28:682688.
  19. Ross MA, Hockenberry JM, Mutter R, Barrett M, Wheatley M, Pitts SR. Protocol‐driven emergency department observation units offer savings, shorter stays, and reduced admissions. Health Aff (Millwood). 2013;32:21492156.
  20. Creswell J, Abelsonjan R. Hospital chain said to scheme to inflate bills. New York Times. January 23, 2014. Available at: http://www.nytimes.com/2014/01/24/business/hospital‐chain‐said‐to‐scheme‐to‐inflate‐bills.html?emc=eta1367:391393.
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Readmissions of Medicare beneficiaries within 30 days of discharge are frequent and costly.[1] Concern about readmissions has prompted the Centers for Medicare & Medicaid Services (CMS) to reduce payments to hospitals with excess readmissions.[2] Research has identified a number of patient clinical and socio‐demographic factors associated with readmissions.[3] However, interventions designed to reduce readmissions have met with limited success. In a systematic review, no single intervention was regularly effective in reducing readmissions, despite the fact that interventions have targeted both predischarge, transition of care, and postdischarge processes of care.[4]

The different trajectories of care experienced by patients after hospital discharge, and their effect on risk of readmission, have been incompletely studied. Although early outpatient follow‐up after discharge is associated with lower readmission rates,[5, 6] a factor that has been minimally studied is the role of the emergency department (ED) and the ED provider in readmissions. The ED and ED providers feature prominently in the care received by patients shortly after discharge from a hospital. About a quarter of all hospitalized Medicare patients are evaluated in an ED within 30 days of discharge,[7, 8] and a majority of readmissions within 30 days of discharge are precipitated by an ED visit.[9] Hence, we asked whether when a recently discharged patient is seen in an ED, does the rate of readmission vary by ED provider and by ED facility?

We used Texas Medicare claims data to examine patients visiting the ED within 30 days of discharge from an initial hospitalization to determine if their risk of readmission varies by the ED provider caring for them and by the ED facility they visit.

METHODS

Sources of Data

We used claims from the years 2007 to 2011 for 100% of Texas Medicare beneficiaries, including Medicare beneficiary summary files, Medicare Provider Analysis and Review (MedPAR) files, Outpatient Standard Analytical Files (OutSAF), and Medicare Carrier files. We obtained diagnosis‐related group associated information, including weights, and Major Diagnostic Category from CMS, and used Provider of Services files to determine facility characteristics.

Establishment of the Study Cohort

From 2008 through 2011 MedPAR files, we initially selected all hospital discharges from acute‐care hospitals in Texas. From these 3,191,160 admissions, we excluded those discharged dead or transferred to other acute‐care hospitals (N=230,343), those who were younger than 66 years at admission (N=736,685) and those without complete Parts A and B enrollment or with any health maintenance organization enrollment in the 12 months prior to and 2 months after the admission of interest (N=596,427). From the remaining 1,627,705 discharges, we identified 302,949 discharges that were followed by at least 1 ED visit within 30 days.

We applied the algorithm developed by Kaskie et al. to identify ED visits.[10] We identified claims for ED services with Current Procedural Terminology (CPT) codes 99281‐99285 from Carrier files and bundled claims with overlapping dates or those that were within 1 day of each other. Then we identified claims for ED services using the same CPT codes from OutSAF and bundled those with overlapping dates or those that were within 3 days of each other. Finally, we bundled Carrier and OutSAF claims with overlapping dates and defined them as the same ED visit. From these, we retained only the first ED visit. We excluded those receiving care from multiple ED providers during the ED visit (N=38,565), and those who had a readmission before the first ED visit (N=1436), leaving 262,948 ED visits. For patients who had more than 1 hospitalization followed by an ED visit in a given year, we selected the first hospitalization, resulting in 199,143 ED visits. We then selected ED providers associated with at least 30 ED visits in this cohort, resulting in 1922 ED providers and 174,209 ED visits. For analyses where we examined both ED provider and facility variation in admission rates, we eliminated ED providers that generated charges from more than 1 ED facility, resulting in 525 providers and 48,883 ED visits at 143 ED facilities.

Measures

Patient Characteristics

We categorized beneficiaries by age, gender, and ethnicity using Medicare beneficiary summary files. We used the Medicaid indicator as a proxy of low socioeconomic status. We obtained information on weekend admission, emergent admission, discharge destination, and diagnosis‐related groupt (DRG) from MedPAR files. We identified comorbidities using the claims from MedPAR, Carrier, and OutSAF files in the year prior to the admission.[11] We identified total hospitalizations and outpatient visits in the prior year from MedPAR files and Carrier files, respectively. We obtained education status at the level of zip code of residence from the 2011 American Community Survey estimates from the United States Census Bureau. We determined urban or rural residence using the 2013 Rural‐Urban Continuum Codes developed by the United States Department of Agriculture.

ED Facility Characteristics

We used the provider number of the ED facility to link to the Provider of Services files and obtained information on medical school affiliation, facility size, and for profit status.

Study Outcomes

The outcome of this study was readmission after an ED visit within 30 days of discharge from an initial hospitalization. We defined readmission after an ED visit as a hospitalization starting the day of or the day following the ED visit

Statistical Analyses

We performed 2‐level analyses where patients were clustered with ED providers to examine variation among ED providers. The effect of ED providers was modeled as a random effect to account for the correlation among the patients cared for by the same ED provider. We derived ED provider‐specific estimates from models adjusted for patient age, gender, race/ethnicity, rural or urban residence, Medicaid eligibility, education at the zip code level of residence, and characteristics of the initial admission (emergency admission, weekend admission, discharge destination, its major diagnostic category and DRG weight). We also adjusted for comorbidities, number of hospitalizations, and number of physician visits in the year before the initial admission.

We also conducted 2‐level analyses where patients were nested in ED facilities and 3‐level analyses where patients were nested in ED providers and ED providers were nested in ED facilities. We adjusted for all factors described above. We computed the change in the variance between 2‐level and 2‐level analyses to determine the variation in readmission rates that was explained by the ED provider and the ED facility. All analyses were performed with SAS version 9.2 (SAS Institute Inc., Cary, NC).

RESULTS

We identified 174,209 patients who visited an ED within 30 days of discharge from an initial hospitalization. Table 1 describes the characteristics of these patients as well as the readmission rates associated with these characteristics. The rate of readmission of our cohort of 1,627,705 discharges with or without a following ED visit was 16.2%, whereas the rate of readmission following an ED visit in our final cohort of 174,209 patients was 52.67%. This readmission rate increased with age, from 49.31% for patients between 66 and 70 years of age to 55.33% for patients older than 85 years. There were minor variations by gender and ethnicity. Patients residing in metropolitan areas or in zip codes with low education levels had higher readmission rates, as did those whose original admission was classified as emergency or those who were not discharged home.

The Effect of Patient Characteristics on the Risk of Hospitalization During an ED Visit Within 30 Days of Hospital Discharge
Patient CharacteristicNo. of ED Visits (%)% ReadmittedOdds Ratio (95% CI)a
 MeanSD, Median (Q1Q3)Odds Ratio (95% CI)a
  • NOTE: There were 141 patients with unknown education level and 22 with unknown place (rural/urban) of residence. These were included as a separate category in the analyses but are not shown. Abbreviations: CI, confidence interval; DGR, diagnosis‐related group; ED, emergency department; SD, standard deviation.

  • Estimated from 2‐level models adjusted for other patient characteristics.

  • Statistically significant results.

  • Percent of persons age 25+ years with high school education or higher at the zip code of residence.

Overall174,209 (100)52.67 
Age, y   
667032,962 (18.92)49.311.00
717534,979 (20.08)51.481.10 (1.06‐1.13)b
768036,728 (21.08)53.011.15 (1.12‐1.19)b
818534,784 (19.97)54.051.19 (1.15‐1.23)b
>8534,756 (19.95)55.331.25 (1.21‐1.29)b
Gender   
Male71,049 (40.78)52.951.02 (1.00‐1.04)
Female103,160 (59.22)52.481.00
Race   
Non‐Hispanic white124,312 (71.36)52.771.00
Black16,809 (9.65)51.450.84 (0.81‐0.87)b
Hispanic30,618 (17.58)52.700.88 (0.85‐0.91)b
Other2,470 (1.42)55.711.06 (0.97‐1.15)
Rural/urban residence   
Metropolitan136,739 (78.49)53.881.00
Nonmetropolitan35,000 (20.09)48.160.96 (0.93‐0.99)b
Rural2,448 (1.41)50.041.04 (0.95‐1.13)
Medicaid eligible   
No128,909 (74.00)52.651.00
Yes45,300 (26.00)52.720.97 (0.94‐0.99)b
Education levelc   
1st quartile (lowest)43,863 (25.18)54.611.00
2nd quartile43,316 (24.86)53.921.00 (0.97‐1.03)
3rd quartile43,571 (25.01)50.720.99 (0.96‐1.02)
4th quartile (highest)43,318 (24.87)51.981.01 (0.97‐1.04)
Emergency admission   
No99,101 (56.89)51.151.00
Yes75,108 (43.11)54.681.07 (1.05‐1.09)b
Weekend admission   
No131,266 (75.35)52.451.00
Yes42,943 (24.65)53.351.01 (0.99‐1.04)
Discharge destination   
Home122,542 (70.34)50.901.00
Inpatient rehabilitation facility9,512 (5.46)55.481.31 (1.25‐1.37)b
Skilled nursing facility37,248 (21.38)57.251.29 (1.26‐1.33)b
Other4,907 (2.82)56.881.14 (1.07‐1.21)b
DRG weight (per unit)1.561.27, 0.82 (1.16‐1.83)1.06 (1.05‐1.07)b
Hospitalization in the prior year (per hospitalization)1.031.49, 0.00 (1.00‐2.00)1.04 (1.03‐1.04)b
Physician visits in the prior year (per 10 visits)11.759.80, 5.00 (10.00‐17.00)0.97 (0.96‐0.98)b

Table 1 also presents the odds of readmission adjusted for all other factors in the table and also adjusted for clustering within ED providers in a 2‐level model. Increasing age, white race, metropolitan residence, nonhome discharge, higher severity of illness, more hospitalizations in the prior year, fewer physician visits in the prior year, and an emergency initial admission were each associated with a higher readmission rate.

We next generated estimates of readmission rates for each ED provider from the adjusted 2‐level models. Figure 1 shows the adjusted cumulative readmission rates for the 1922 ED providers. This figure shows the mean value and 95% confidence intervals of the readmission rates for each provider. Dark vertical lines indicate providers whose readmission rate differed significantly from the mean adjusted readmission rate of 52.1% for all providers. Of the ED providers, 14.2% had significantly higher readmission rates. The mean readmission rate for these 272 providers was 67.2%. Of the ED providers, 14.7% had significantly lower readmission rates. The mean readmission rate for these 283 providers was 36.8%.

Figure 1
Ranking of emergency department (ED) provider by adjusted readmission rate: readmission on the day of or day after ED visit. Rates were estimated by 2‐level analyses, adjusted for patient characteristics. The horizontal line represents the overall mean. Error bars represent 95% confidence intervals of the estimate for the individual ED provider. Black error bars represent ED providers with significantly higher or lower estimates.

To determine the contribution of the ED facility to the variation in readmission rates, we restricted our analysis to 48,883 patients (28.06% of our cohort) seen by 525 ED providers who were associated with only 1 facility (total of 143 facilities). Table 2 describes the unadjusted readmission rates stratified by specific characteristics of those facilities. The unadjusted readmission rate increased with the size of the associated hospital, from 47.61% for hospitals with less than 100 beds to 57.06% for hospitals with more than 400 beds. The readmission rate for nonprofit facilities was 53.81% and for for‐profit facilities was 57.39%. Facilities with no medical school affiliation had a readmission rate of 54.51%, whereas those with a major affiliation had a readmission rate of 58.72%.

The Effect of ED Facility Characteristics on the Risk of Readmission After an ED Visit
ED Facility CharacteristicNo. of ED Visits (%)% ReadmittedOdds Ratio (95% CI)a
  • NOTE: Abbreviations: CI, confidence interval; ED, emergency department.

  • Estimated from 3‐level models adjusted for patient characteristics. ED providers associated with only 1 hospital from 2008 through 2011 were selected for the 3‐level analyses. There were 525 ED providers from 143 facilities.

  • Statistically significant results.

Overall48,883  
Total beds   
1003,936 (8.05)47.611.00
1012006,251 (12.79)52.071.38 (1.06‐1.81)b
20140013,000 (26.59)56.261.69 (1.32‐2.17)b
>40025,696 (52.57)57.061.77 (1.35‐2.33)b
Type of control   
Nonprofit24,999 (51.14)53.811.00
Proprietary17,108 (35.00)57.391.32 (1.09‐1.61)b
Government6,776 (13.86)56.601.11 (0.88‐1.41)
Medical school affiliation   
Major6,487 (13.27)58.721.00
Limited7,066 (14.45)56.370.85 (0.58‐1.25)
Graduate3,164 (6.47)56.190.71 (0.44‐1.15)
No affiliation32,166 (65.80)54.510.78 (0.57‐1.05)
If the same hospital patient was discharged from   
Yes38,532 (78.82)55.640.96 (0.91‐1.00)
No10,351 (21.18)54.731.00

With this smaller cohort, we performed 2 types of 2‐level models, where patients clustered within ED facilities and ER providers, respectively, and a 3‐level model accounting for clustering of patients within providers and of providers within facilities. From the facility‐patient 2‐level model, the variance of the ED facility was 0.2718 (95% confidence interval [CI]: 0.2083‐0.3696). From the provider‐patient 2‐level model, the variance of ED provider was 0.2532 (95% CI: 0.2166‐0.3002). However, when the 3‐level model was performed, the variance of ED provider decreased to 0.0893 (95% CI: 0.0723‐0.1132) and the variance of ED facility dropped to 0.2316 (95% CI: 0.1704‐0.3331) . This indicates 65% of the variation among ED providers was explained by the ED facility, and in contrast, 15% of the variation among ED facilities was explained by ED providers.

Table 2 also shows the adjusted odds of readmission generated from the 3‐level model. Patients receiving care in ED facilities in hospitals with more beds and in for‐profit hospitals were at higher risk for readmission. It is possible that patients seen at the ED associated with the discharging hospital had a lower risk of readmission. This finding was close to being statistically significant (P=0.051).

We repeated all the above analyses using an outcome of readmission anytime between the ED visit and 30 days after discharge from the initial hospitalization (rather than readmission on the day of or after the ED visit). All analyses produced results similar to the results presented above. For example, Figure 2 shows the adjusted cumulative readmission rates for the 1922 ED providers using this outcome. Of the ED providers, 12.8% had higher and 12.5% had lower readmission rates as compared to the mean readmission rate for all ED providers. The Spearman correlation coefficient between the rank of ED providers in immediate readmission rate (Figure 1) and readmission rate within 30 days of hospital discharge (Figure 2) was 0.94 (P<0.001).

Figure 2
Ranking of emergency department (ED) provider by adjusted readmission rate: readmission after an ED visit but anytime within 30 days of discharge from initial hospitalization. Rates were estimated by 2‐level analyses, adjusted for patient characteristics. The horizontal line represents the overall mean. Error bars represent 95% confidence intervals of the estimate for the individual ED provider. Black error bars represent ED providers with significantly higher or lower estimates.

DISCUSSION

This study found substantial variation in readmission rates by ED provider, despite controlling for patient clinical and sociodemographic factors. In 3‐level models, the ED facility explained a substantial part of the variation by ED provider, with patients seen at larger facilities and for‐profit facilities having higher readmission rates.

Variation among ED facilities and ED providers in readmission rates has not previously been studied. There is literature on the variation in ED facility and ED provider admission rates. As readmissions are a subset of all admissions, this literature provides context to our findings. Abualenain et al. examined admission rates for 89 ED physicians for adult patients presenting with an acute medical or surgical complaint at 3 EDs in a health system.[12] After adjusting for patient and clinical characteristics, admission rates varied from 21% to 49% among physicians and from 27% to 41% among 3 facilities. Two other studies from single hospitals have found similar variation among providers.[13, 14] The reasons for the variation among ED providers presumably relate to subjective aspects of clinical assessment and the reluctance of providers to rely solely on objective scales, even when they are available.[14, 15] Variation in admission rates among different facilities may relate to clustering of providers with similar practice styles within facilities, lack of clinical guidelines for certain conditions, as well as differences among facilities in the socioeconomic status and access to primary care of their clientele.[12, 16, 17] For example, Pines et al. have shown that ED facility admission rates are higher in communities with fewer primary care physicians per capita and are influenced by the prevailing county level admission rates.[16] Capp et al. showed persistent variation in admission rates across hospitals, despite adjusting for clinical criteria such as vital signs, chief complaints, and severity of illness.[18]

Structural differences in ED facilities may also influence the decision to admit. We found that patients visiting ED facilities in hospitals with more beds had a higher readmission rate. ED facility systems of care such as observation units or protocols are associated with lower admission rates.[19, 20] Finally, certain hospitals may actively influence the admission practice patterns of their ED providers. We noted that patients seen at for‐profit ED facilities had a greater risk of readmission. A similar finding has been described by Pines et al., who noted higher admission rates at for‐profit facilities.[16] In an extreme example, a recent Justice Department lawsuit alleged that a for‐profit hospital chain used software systems and financial incentives to ED providers to increase admissions.[21]

It is possible that the providers with low readmission rates may have inappropriately released patients who truly should have been admitted. A signal that this occurred would be if these patients were readmitted in the days after the ED visits. We examined this possibility by additionally examining readmissions occurring anytime between the ED visit until 30 days after discharge from the initial hospitalization. The results were similar to when we only included readmissions that occurred immediately following the ED visit, with a very high correlation (r=0.94) between the ranking of the ED providers by readmission rates in both circumstances. This suggests that the decisions of the ED providers with low readmission rates to admit or release from the ED were likely appropriate.

Our research has limitations. We studied patients with fee‐for‐service Medicare in a single large state in the United States over a 4‐year period. Our findings may not be generalizable to younger patient populations, other regions with different sociodemographic patterns and healthcare systems, or other time periods. We could not control for many factors that may impact the risk of readmission but are not measured in Medicare databases (eg, clinical data such as vital signs, measures of quality of transition from discharging hospital, ED provider workload). To attribute care to a single ED provider, we excluded patients who were taken care of by multiple ED providers. These patients may have different needs from our study population (eg, more complex issues and longer stays in the ED) and may bias our results.

This study provides a new direction for research and quality improvement targeting readmissions. Research should extend beyond the discharge transition and examine the entire trajectory of posthospitalization care to better understand readmissions. Based directly on this study, research could investigate the practice patterns of ED providers and systems of care at ED facilities that affect readmissions rates. Such investigation could inform quality improvement efforts to standardize care for patients in the ED.

CMS policies hold hospitals accountable for readmissions of the patients they discharge, but do not address the admission process in the ED that leads to readmissions of recently discharged patients. Given the present study, and the fact that the proportion of all hospital admissions that occur through the ED has grown to 44%,[22] consideration of the role of the ED in public policy efforts to discourage unnecessary inpatient care may be appropriate.

In summary, this study shows that a recently discharged patient's chances of being readmitted depends partly on the ED provider who evaluates them and on the ED facility at which they seek care. ED provider practice patterns and ED facility systems of care may be a target for interventions aimed at decreasing readmission rates.

Disclosures

This research was supported by grants from the National Institutes of Health (AG033134 and K05CA134923) and from the Agency for Healthcare Research and Quality (R24H5022134). The authors report no conflicts of interest.

Readmissions of Medicare beneficiaries within 30 days of discharge are frequent and costly.[1] Concern about readmissions has prompted the Centers for Medicare & Medicaid Services (CMS) to reduce payments to hospitals with excess readmissions.[2] Research has identified a number of patient clinical and socio‐demographic factors associated with readmissions.[3] However, interventions designed to reduce readmissions have met with limited success. In a systematic review, no single intervention was regularly effective in reducing readmissions, despite the fact that interventions have targeted both predischarge, transition of care, and postdischarge processes of care.[4]

The different trajectories of care experienced by patients after hospital discharge, and their effect on risk of readmission, have been incompletely studied. Although early outpatient follow‐up after discharge is associated with lower readmission rates,[5, 6] a factor that has been minimally studied is the role of the emergency department (ED) and the ED provider in readmissions. The ED and ED providers feature prominently in the care received by patients shortly after discharge from a hospital. About a quarter of all hospitalized Medicare patients are evaluated in an ED within 30 days of discharge,[7, 8] and a majority of readmissions within 30 days of discharge are precipitated by an ED visit.[9] Hence, we asked whether when a recently discharged patient is seen in an ED, does the rate of readmission vary by ED provider and by ED facility?

We used Texas Medicare claims data to examine patients visiting the ED within 30 days of discharge from an initial hospitalization to determine if their risk of readmission varies by the ED provider caring for them and by the ED facility they visit.

METHODS

Sources of Data

We used claims from the years 2007 to 2011 for 100% of Texas Medicare beneficiaries, including Medicare beneficiary summary files, Medicare Provider Analysis and Review (MedPAR) files, Outpatient Standard Analytical Files (OutSAF), and Medicare Carrier files. We obtained diagnosis‐related group associated information, including weights, and Major Diagnostic Category from CMS, and used Provider of Services files to determine facility characteristics.

Establishment of the Study Cohort

From 2008 through 2011 MedPAR files, we initially selected all hospital discharges from acute‐care hospitals in Texas. From these 3,191,160 admissions, we excluded those discharged dead or transferred to other acute‐care hospitals (N=230,343), those who were younger than 66 years at admission (N=736,685) and those without complete Parts A and B enrollment or with any health maintenance organization enrollment in the 12 months prior to and 2 months after the admission of interest (N=596,427). From the remaining 1,627,705 discharges, we identified 302,949 discharges that were followed by at least 1 ED visit within 30 days.

We applied the algorithm developed by Kaskie et al. to identify ED visits.[10] We identified claims for ED services with Current Procedural Terminology (CPT) codes 99281‐99285 from Carrier files and bundled claims with overlapping dates or those that were within 1 day of each other. Then we identified claims for ED services using the same CPT codes from OutSAF and bundled those with overlapping dates or those that were within 3 days of each other. Finally, we bundled Carrier and OutSAF claims with overlapping dates and defined them as the same ED visit. From these, we retained only the first ED visit. We excluded those receiving care from multiple ED providers during the ED visit (N=38,565), and those who had a readmission before the first ED visit (N=1436), leaving 262,948 ED visits. For patients who had more than 1 hospitalization followed by an ED visit in a given year, we selected the first hospitalization, resulting in 199,143 ED visits. We then selected ED providers associated with at least 30 ED visits in this cohort, resulting in 1922 ED providers and 174,209 ED visits. For analyses where we examined both ED provider and facility variation in admission rates, we eliminated ED providers that generated charges from more than 1 ED facility, resulting in 525 providers and 48,883 ED visits at 143 ED facilities.

Measures

Patient Characteristics

We categorized beneficiaries by age, gender, and ethnicity using Medicare beneficiary summary files. We used the Medicaid indicator as a proxy of low socioeconomic status. We obtained information on weekend admission, emergent admission, discharge destination, and diagnosis‐related groupt (DRG) from MedPAR files. We identified comorbidities using the claims from MedPAR, Carrier, and OutSAF files in the year prior to the admission.[11] We identified total hospitalizations and outpatient visits in the prior year from MedPAR files and Carrier files, respectively. We obtained education status at the level of zip code of residence from the 2011 American Community Survey estimates from the United States Census Bureau. We determined urban or rural residence using the 2013 Rural‐Urban Continuum Codes developed by the United States Department of Agriculture.

ED Facility Characteristics

We used the provider number of the ED facility to link to the Provider of Services files and obtained information on medical school affiliation, facility size, and for profit status.

Study Outcomes

The outcome of this study was readmission after an ED visit within 30 days of discharge from an initial hospitalization. We defined readmission after an ED visit as a hospitalization starting the day of or the day following the ED visit

Statistical Analyses

We performed 2‐level analyses where patients were clustered with ED providers to examine variation among ED providers. The effect of ED providers was modeled as a random effect to account for the correlation among the patients cared for by the same ED provider. We derived ED provider‐specific estimates from models adjusted for patient age, gender, race/ethnicity, rural or urban residence, Medicaid eligibility, education at the zip code level of residence, and characteristics of the initial admission (emergency admission, weekend admission, discharge destination, its major diagnostic category and DRG weight). We also adjusted for comorbidities, number of hospitalizations, and number of physician visits in the year before the initial admission.

We also conducted 2‐level analyses where patients were nested in ED facilities and 3‐level analyses where patients were nested in ED providers and ED providers were nested in ED facilities. We adjusted for all factors described above. We computed the change in the variance between 2‐level and 2‐level analyses to determine the variation in readmission rates that was explained by the ED provider and the ED facility. All analyses were performed with SAS version 9.2 (SAS Institute Inc., Cary, NC).

RESULTS

We identified 174,209 patients who visited an ED within 30 days of discharge from an initial hospitalization. Table 1 describes the characteristics of these patients as well as the readmission rates associated with these characteristics. The rate of readmission of our cohort of 1,627,705 discharges with or without a following ED visit was 16.2%, whereas the rate of readmission following an ED visit in our final cohort of 174,209 patients was 52.67%. This readmission rate increased with age, from 49.31% for patients between 66 and 70 years of age to 55.33% for patients older than 85 years. There were minor variations by gender and ethnicity. Patients residing in metropolitan areas or in zip codes with low education levels had higher readmission rates, as did those whose original admission was classified as emergency or those who were not discharged home.

The Effect of Patient Characteristics on the Risk of Hospitalization During an ED Visit Within 30 Days of Hospital Discharge
Patient CharacteristicNo. of ED Visits (%)% ReadmittedOdds Ratio (95% CI)a
 MeanSD, Median (Q1Q3)Odds Ratio (95% CI)a
  • NOTE: There were 141 patients with unknown education level and 22 with unknown place (rural/urban) of residence. These were included as a separate category in the analyses but are not shown. Abbreviations: CI, confidence interval; DGR, diagnosis‐related group; ED, emergency department; SD, standard deviation.

  • Estimated from 2‐level models adjusted for other patient characteristics.

  • Statistically significant results.

  • Percent of persons age 25+ years with high school education or higher at the zip code of residence.

Overall174,209 (100)52.67 
Age, y   
667032,962 (18.92)49.311.00
717534,979 (20.08)51.481.10 (1.06‐1.13)b
768036,728 (21.08)53.011.15 (1.12‐1.19)b
818534,784 (19.97)54.051.19 (1.15‐1.23)b
>8534,756 (19.95)55.331.25 (1.21‐1.29)b
Gender   
Male71,049 (40.78)52.951.02 (1.00‐1.04)
Female103,160 (59.22)52.481.00
Race   
Non‐Hispanic white124,312 (71.36)52.771.00
Black16,809 (9.65)51.450.84 (0.81‐0.87)b
Hispanic30,618 (17.58)52.700.88 (0.85‐0.91)b
Other2,470 (1.42)55.711.06 (0.97‐1.15)
Rural/urban residence   
Metropolitan136,739 (78.49)53.881.00
Nonmetropolitan35,000 (20.09)48.160.96 (0.93‐0.99)b
Rural2,448 (1.41)50.041.04 (0.95‐1.13)
Medicaid eligible   
No128,909 (74.00)52.651.00
Yes45,300 (26.00)52.720.97 (0.94‐0.99)b
Education levelc   
1st quartile (lowest)43,863 (25.18)54.611.00
2nd quartile43,316 (24.86)53.921.00 (0.97‐1.03)
3rd quartile43,571 (25.01)50.720.99 (0.96‐1.02)
4th quartile (highest)43,318 (24.87)51.981.01 (0.97‐1.04)
Emergency admission   
No99,101 (56.89)51.151.00
Yes75,108 (43.11)54.681.07 (1.05‐1.09)b
Weekend admission   
No131,266 (75.35)52.451.00
Yes42,943 (24.65)53.351.01 (0.99‐1.04)
Discharge destination   
Home122,542 (70.34)50.901.00
Inpatient rehabilitation facility9,512 (5.46)55.481.31 (1.25‐1.37)b
Skilled nursing facility37,248 (21.38)57.251.29 (1.26‐1.33)b
Other4,907 (2.82)56.881.14 (1.07‐1.21)b
DRG weight (per unit)1.561.27, 0.82 (1.16‐1.83)1.06 (1.05‐1.07)b
Hospitalization in the prior year (per hospitalization)1.031.49, 0.00 (1.00‐2.00)1.04 (1.03‐1.04)b
Physician visits in the prior year (per 10 visits)11.759.80, 5.00 (10.00‐17.00)0.97 (0.96‐0.98)b

Table 1 also presents the odds of readmission adjusted for all other factors in the table and also adjusted for clustering within ED providers in a 2‐level model. Increasing age, white race, metropolitan residence, nonhome discharge, higher severity of illness, more hospitalizations in the prior year, fewer physician visits in the prior year, and an emergency initial admission were each associated with a higher readmission rate.

We next generated estimates of readmission rates for each ED provider from the adjusted 2‐level models. Figure 1 shows the adjusted cumulative readmission rates for the 1922 ED providers. This figure shows the mean value and 95% confidence intervals of the readmission rates for each provider. Dark vertical lines indicate providers whose readmission rate differed significantly from the mean adjusted readmission rate of 52.1% for all providers. Of the ED providers, 14.2% had significantly higher readmission rates. The mean readmission rate for these 272 providers was 67.2%. Of the ED providers, 14.7% had significantly lower readmission rates. The mean readmission rate for these 283 providers was 36.8%.

Figure 1
Ranking of emergency department (ED) provider by adjusted readmission rate: readmission on the day of or day after ED visit. Rates were estimated by 2‐level analyses, adjusted for patient characteristics. The horizontal line represents the overall mean. Error bars represent 95% confidence intervals of the estimate for the individual ED provider. Black error bars represent ED providers with significantly higher or lower estimates.

To determine the contribution of the ED facility to the variation in readmission rates, we restricted our analysis to 48,883 patients (28.06% of our cohort) seen by 525 ED providers who were associated with only 1 facility (total of 143 facilities). Table 2 describes the unadjusted readmission rates stratified by specific characteristics of those facilities. The unadjusted readmission rate increased with the size of the associated hospital, from 47.61% for hospitals with less than 100 beds to 57.06% for hospitals with more than 400 beds. The readmission rate for nonprofit facilities was 53.81% and for for‐profit facilities was 57.39%. Facilities with no medical school affiliation had a readmission rate of 54.51%, whereas those with a major affiliation had a readmission rate of 58.72%.

The Effect of ED Facility Characteristics on the Risk of Readmission After an ED Visit
ED Facility CharacteristicNo. of ED Visits (%)% ReadmittedOdds Ratio (95% CI)a
  • NOTE: Abbreviations: CI, confidence interval; ED, emergency department.

  • Estimated from 3‐level models adjusted for patient characteristics. ED providers associated with only 1 hospital from 2008 through 2011 were selected for the 3‐level analyses. There were 525 ED providers from 143 facilities.

  • Statistically significant results.

Overall48,883  
Total beds   
1003,936 (8.05)47.611.00
1012006,251 (12.79)52.071.38 (1.06‐1.81)b
20140013,000 (26.59)56.261.69 (1.32‐2.17)b
>40025,696 (52.57)57.061.77 (1.35‐2.33)b
Type of control   
Nonprofit24,999 (51.14)53.811.00
Proprietary17,108 (35.00)57.391.32 (1.09‐1.61)b
Government6,776 (13.86)56.601.11 (0.88‐1.41)
Medical school affiliation   
Major6,487 (13.27)58.721.00
Limited7,066 (14.45)56.370.85 (0.58‐1.25)
Graduate3,164 (6.47)56.190.71 (0.44‐1.15)
No affiliation32,166 (65.80)54.510.78 (0.57‐1.05)
If the same hospital patient was discharged from   
Yes38,532 (78.82)55.640.96 (0.91‐1.00)
No10,351 (21.18)54.731.00

With this smaller cohort, we performed 2 types of 2‐level models, where patients clustered within ED facilities and ER providers, respectively, and a 3‐level model accounting for clustering of patients within providers and of providers within facilities. From the facility‐patient 2‐level model, the variance of the ED facility was 0.2718 (95% confidence interval [CI]: 0.2083‐0.3696). From the provider‐patient 2‐level model, the variance of ED provider was 0.2532 (95% CI: 0.2166‐0.3002). However, when the 3‐level model was performed, the variance of ED provider decreased to 0.0893 (95% CI: 0.0723‐0.1132) and the variance of ED facility dropped to 0.2316 (95% CI: 0.1704‐0.3331) . This indicates 65% of the variation among ED providers was explained by the ED facility, and in contrast, 15% of the variation among ED facilities was explained by ED providers.

Table 2 also shows the adjusted odds of readmission generated from the 3‐level model. Patients receiving care in ED facilities in hospitals with more beds and in for‐profit hospitals were at higher risk for readmission. It is possible that patients seen at the ED associated with the discharging hospital had a lower risk of readmission. This finding was close to being statistically significant (P=0.051).

We repeated all the above analyses using an outcome of readmission anytime between the ED visit and 30 days after discharge from the initial hospitalization (rather than readmission on the day of or after the ED visit). All analyses produced results similar to the results presented above. For example, Figure 2 shows the adjusted cumulative readmission rates for the 1922 ED providers using this outcome. Of the ED providers, 12.8% had higher and 12.5% had lower readmission rates as compared to the mean readmission rate for all ED providers. The Spearman correlation coefficient between the rank of ED providers in immediate readmission rate (Figure 1) and readmission rate within 30 days of hospital discharge (Figure 2) was 0.94 (P<0.001).

Figure 2
Ranking of emergency department (ED) provider by adjusted readmission rate: readmission after an ED visit but anytime within 30 days of discharge from initial hospitalization. Rates were estimated by 2‐level analyses, adjusted for patient characteristics. The horizontal line represents the overall mean. Error bars represent 95% confidence intervals of the estimate for the individual ED provider. Black error bars represent ED providers with significantly higher or lower estimates.

DISCUSSION

This study found substantial variation in readmission rates by ED provider, despite controlling for patient clinical and sociodemographic factors. In 3‐level models, the ED facility explained a substantial part of the variation by ED provider, with patients seen at larger facilities and for‐profit facilities having higher readmission rates.

Variation among ED facilities and ED providers in readmission rates has not previously been studied. There is literature on the variation in ED facility and ED provider admission rates. As readmissions are a subset of all admissions, this literature provides context to our findings. Abualenain et al. examined admission rates for 89 ED physicians for adult patients presenting with an acute medical or surgical complaint at 3 EDs in a health system.[12] After adjusting for patient and clinical characteristics, admission rates varied from 21% to 49% among physicians and from 27% to 41% among 3 facilities. Two other studies from single hospitals have found similar variation among providers.[13, 14] The reasons for the variation among ED providers presumably relate to subjective aspects of clinical assessment and the reluctance of providers to rely solely on objective scales, even when they are available.[14, 15] Variation in admission rates among different facilities may relate to clustering of providers with similar practice styles within facilities, lack of clinical guidelines for certain conditions, as well as differences among facilities in the socioeconomic status and access to primary care of their clientele.[12, 16, 17] For example, Pines et al. have shown that ED facility admission rates are higher in communities with fewer primary care physicians per capita and are influenced by the prevailing county level admission rates.[16] Capp et al. showed persistent variation in admission rates across hospitals, despite adjusting for clinical criteria such as vital signs, chief complaints, and severity of illness.[18]

Structural differences in ED facilities may also influence the decision to admit. We found that patients visiting ED facilities in hospitals with more beds had a higher readmission rate. ED facility systems of care such as observation units or protocols are associated with lower admission rates.[19, 20] Finally, certain hospitals may actively influence the admission practice patterns of their ED providers. We noted that patients seen at for‐profit ED facilities had a greater risk of readmission. A similar finding has been described by Pines et al., who noted higher admission rates at for‐profit facilities.[16] In an extreme example, a recent Justice Department lawsuit alleged that a for‐profit hospital chain used software systems and financial incentives to ED providers to increase admissions.[21]

It is possible that the providers with low readmission rates may have inappropriately released patients who truly should have been admitted. A signal that this occurred would be if these patients were readmitted in the days after the ED visits. We examined this possibility by additionally examining readmissions occurring anytime between the ED visit until 30 days after discharge from the initial hospitalization. The results were similar to when we only included readmissions that occurred immediately following the ED visit, with a very high correlation (r=0.94) between the ranking of the ED providers by readmission rates in both circumstances. This suggests that the decisions of the ED providers with low readmission rates to admit or release from the ED were likely appropriate.

Our research has limitations. We studied patients with fee‐for‐service Medicare in a single large state in the United States over a 4‐year period. Our findings may not be generalizable to younger patient populations, other regions with different sociodemographic patterns and healthcare systems, or other time periods. We could not control for many factors that may impact the risk of readmission but are not measured in Medicare databases (eg, clinical data such as vital signs, measures of quality of transition from discharging hospital, ED provider workload). To attribute care to a single ED provider, we excluded patients who were taken care of by multiple ED providers. These patients may have different needs from our study population (eg, more complex issues and longer stays in the ED) and may bias our results.

This study provides a new direction for research and quality improvement targeting readmissions. Research should extend beyond the discharge transition and examine the entire trajectory of posthospitalization care to better understand readmissions. Based directly on this study, research could investigate the practice patterns of ED providers and systems of care at ED facilities that affect readmissions rates. Such investigation could inform quality improvement efforts to standardize care for patients in the ED.

CMS policies hold hospitals accountable for readmissions of the patients they discharge, but do not address the admission process in the ED that leads to readmissions of recently discharged patients. Given the present study, and the fact that the proportion of all hospital admissions that occur through the ED has grown to 44%,[22] consideration of the role of the ED in public policy efforts to discourage unnecessary inpatient care may be appropriate.

In summary, this study shows that a recently discharged patient's chances of being readmitted depends partly on the ED provider who evaluates them and on the ED facility at which they seek care. ED provider practice patterns and ED facility systems of care may be a target for interventions aimed at decreasing readmission rates.

Disclosures

This research was supported by grants from the National Institutes of Health (AG033134 and K05CA134923) and from the Agency for Healthcare Research and Quality (R24H5022134). The authors report no conflicts of interest.

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  2. Centers for Medicare 306:16881698.
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  4. Sharma G, Kuo Y, Freeman JL, Zhang DD, Goodwin JS. Outpatient follow‐up visit and 30‐day emergency department visit and readmission in patients hospitalized for chronic obstructive pulmonary disease. Arch Intern Med. 2010;170:16641670.
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  13. Mutrie D, Bailey SK, Malik S. Individual emergency physician admission rates: predictably unpredictable. CJEM. 2009;11(2):149155.
  14. Aujesky D, McCausland JB, Whittle J, Obrosky DS, Yealy DM, Fine MJ. Reasons why emergency department providers do not rely on the pneumonia severity index to determine the initial site of treatment for patients with pneumonia. Clin Infect Dis. 2009;49:e100e108.
  15. Pines JM, Mutter RL, Zocchi MS. Variation in emergency department admission rates across the United States. Med Care Res Rev. 2013;70:218231.
  16. Venkatesh AK, Dai Y, Ross JS, Schuur JD, Capp R, Krumholz HM. Variation in US hospital emergency department admission rates by clinical condition. Med Care. 2015;53:237244.
  17. Capp R, Ross JS, Fox JP, et al. Hospital variation in risk‐standardized hospital admission rates from US EDs among adults. Am J Emerg Med. 2014;32:837843.
  18. Schrock JW, Reznikova S, Weller S. The effect of an observation unit on the rate of ED admission and discharge for pyelonephritis. Am J Emerg Med. 2010;28:682688.
  19. Ross MA, Hockenberry JM, Mutter R, Barrett M, Wheatley M, Pitts SR. Protocol‐driven emergency department observation units offer savings, shorter stays, and reduced admissions. Health Aff (Millwood). 2013;32:21492156.
  20. Creswell J, Abelsonjan R. Hospital chain said to scheme to inflate bills. New York Times. January 23, 2014. Available at: http://www.nytimes.com/2014/01/24/business/hospital‐chain‐said‐to‐scheme‐to‐inflate‐bills.html?emc=eta1367:391393.
References
  1. Jencks SF, Williams MV, Coleman EA. Rehospitalizations among patients in the Medicare Fee‐for‐Service Program. N Engl J Med. 2009;360:14181428.
  2. Centers for Medicare 306:16881698.
  3. Hansen LO, Young RS, Hinami K, Leung A, Williams MV. Interventions to reduce 30‐day rehospitalization: a systematic review. Ann Intern Med. 2011;155:520528.
  4. Sharma G, Kuo Y, Freeman JL, Zhang DD, Goodwin JS. Outpatient follow‐up visit and 30‐day emergency department visit and readmission in patients hospitalized for chronic obstructive pulmonary disease. Arch Intern Med. 2010;170:16641670.
  5. Hernandez AF, Greiner MA, Fonarow GC, et al. Relationship between early physician follow‐up and 30‐day readmission among Medicare beneficiaries hospitalized for heart failure. JAMA. 2010;303:17161722.
  6. Goodman DC, Fisher ES, Chang C. After hospitalization: a Dartmouth Atlas report on post‐acute care for Medicare beneficiaries. Dartmouth Atlas website. Available at: www.dartmouthatlas.org/downloads/reports/Post_discharge_events_092811.pdf. Accessed August 8, 2013.
  7. Rising KL, White LF, Fernandez WG, Boutwell AE. Emergency department visits after hospital discharge: a missing part of the equation. Ann Emerg Med. 2013;62:145150.
  8. Kocher KE, Nallamothu BK, Birkmeyer JD, Dimick JB. Emergency department visits after surgery are common for Medicare patients, suggesting opportunities to improve care. Health Aff (Millwood). 2013;32:16001607.
  9. Kaskie B, Obrizan M, Cook E, et al. Defining emergency department episodes by severity and intensity: a 15‐year study of Medicare beneficiaries. BMC Health Serv Res. 2010;10:113.
  10. Elixhauser A, Steiner C, Harris DR, Coffey RM. Comorbidity measures for use with administrative data. Med Care. 1998;36:827.
  11. Abualenain J, Frohna WJ, Shesser R, Ding R, Smith M, Pines JM. Emergency department physician‐level and hospital‐level variation in admission rates. Ann Emerg Med. 2013;61:638643.
  12. Dean NC, Jones JP, Aronsky D, et al. Hospital admission decision for patients with community‐acquired pneumonia: variability among physicians in an emergency department. Ann Emerg Med. 2012;59:3541.
  13. Mutrie D, Bailey SK, Malik S. Individual emergency physician admission rates: predictably unpredictable. CJEM. 2009;11(2):149155.
  14. Aujesky D, McCausland JB, Whittle J, Obrosky DS, Yealy DM, Fine MJ. Reasons why emergency department providers do not rely on the pneumonia severity index to determine the initial site of treatment for patients with pneumonia. Clin Infect Dis. 2009;49:e100e108.
  15. Pines JM, Mutter RL, Zocchi MS. Variation in emergency department admission rates across the United States. Med Care Res Rev. 2013;70:218231.
  16. Venkatesh AK, Dai Y, Ross JS, Schuur JD, Capp R, Krumholz HM. Variation in US hospital emergency department admission rates by clinical condition. Med Care. 2015;53:237244.
  17. Capp R, Ross JS, Fox JP, et al. Hospital variation in risk‐standardized hospital admission rates from US EDs among adults. Am J Emerg Med. 2014;32:837843.
  18. Schrock JW, Reznikova S, Weller S. The effect of an observation unit on the rate of ED admission and discharge for pyelonephritis. Am J Emerg Med. 2010;28:682688.
  19. Ross MA, Hockenberry JM, Mutter R, Barrett M, Wheatley M, Pitts SR. Protocol‐driven emergency department observation units offer savings, shorter stays, and reduced admissions. Health Aff (Millwood). 2013;32:21492156.
  20. Creswell J, Abelsonjan R. Hospital chain said to scheme to inflate bills. New York Times. January 23, 2014. Available at: http://www.nytimes.com/2014/01/24/business/hospital‐chain‐said‐to‐scheme‐to‐inflate‐bills.html?emc=eta1367:391393.
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Variation in readmission rates by emergency departments and emergency department providers caring for patients after discharge
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Address for correspondence and reprint requests: Siddhartha Singh, MD, The Medical College of Wisconsin, 9200 West Wisconsin Avenue, Milwaukee, WI, 53226; Telephone: 414‐805‐0844; Fax: 414‐805‐0454; E‐mail: [email protected]
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Weekend Discharge and Readmission

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Is weekend discharge associated with hospital readmission?

Hospital readmission, defined as an admission to a hospital within 30 days of discharge from an acute‐care hospitalization, is associated with short‐term morbidity, mortality, and medical costs.[1] In 2013, the Patient Protection and Affordable Care Act began assigning financial penalties to hospitals based on performance against benchmarks on readmission for acute myocardial infarction (AMI), pneumonia (PNA), and congestive heart failure (CHF) through its Hospital Readmission Reduction Program (HRRP).[2] In its third year, the program recently announced penalties for 2,610 hospitals that will total over $428 million.[3] Despite increased attention to this issue, few interventions have been identified that effectively reduce hospital readmissions.[4, 5]

Hospital discharge is a complex process that aims to achieve the safe transfer of care of a hospitalized patient to another setting (eg, home, skilled nursing facility [SNF]). Success depends on adequate staffing of physicians, nurses, case managers, social workers, and pharmacists; clear communication among patients and providers; and integrated coordination of care. Although much focus has been placed on the association between weekend hospital admission and increased mortality,[6, 7, 8] very little is known about the impact of weekend hospital discharge on outcomes, specifically hospital readmission rates. Furthermore, previous studies on this topic, based on Canadian data, have produced conflicting results.[9, 10, 11]

Staffing of physicians, physician extenders (eg, physician assistants or nurse practitioners), nurses, case managers, social workers, and ancillary staff (eg, physical and occupational therapists) are all typically reduced on the weekend. Patients may be cared for by covering healthcare providers. These factors may have important implications on the timeliness of discharge, accuracy of discharge instructions, safety of discharge (eg, clearance by physical therapy), and medication reconciliation, among others. Clinic offices are more likely to be closed, and therefore, some follow‐up appointments may inadvertently not be scheduled, and lack of timely postdischarge follow‐up may be associated with higher rates of readmission.[12] Reduced outpatient pharmacy availability may also cause delays in patients receiving their medications,[13] which may exacerbate failed transition to the outpatient setting due to medication noncompliance.[14]

Based on this rationale, the current study was designed to investigate the association between weekend discharge and 30‐ and 90‐ day readmissions in patients hospitalized for medical diagnoses included in Centers for Medicare and Medicaid Services' HRRP.[15] To do so, a large‐state, all‐payer discharge database with individual patient record linkage numbers (RLN) was selected to capture all readmissions, even those to a different hospital. We hypothesized that patients who are discharged on a weekend would have higher hospital readmission rates compared to those discharged on a weekday.

METHODS

Approval was obtained from both the California Committee for the Protection of Human Subjects and the Stanford University Institutional Review Board. The California Office of State Health Planning and Development (OSHPD) 2012 Patient Discharge Data (PDD) was utilized for this study. The OSHPD‐PDD contains records for all patients admitted and eventually discharged from every general, acute, nonfederal hospital within the state. Demographic variables contained in the dataset include age, gender, race, and a unique RLN (an individually assigned number based on the patient's social security number and other demographics) to associate discharged patients with subsequent hospitalizations. Clinical information collected included principal diagnosis (indication for admission), 24 additional diagnoses with an indicator as to whether or not the condition was present on admission (POA) to differentiate comorbidities from complications, and principle procedure codes. Details about the admission included date of admission and discharge, admission type (scheduled or unscheduled), expected payer/emnsurance and disposition (home, acute rehabilitation, skilled nursing facility, residential facility, other). Details about the hospital included a unique identification number to indicate the location of care for both index/discharge and subsequent readmission.

International Classification of Disease, Ninth Edition, Clinical Modification (ICD‐9‐CM) coding schema were used to identify all patients admitted with the principal diagnosis of AMI (ICD‐9‐CM code 410.xx), CHF (428.xx), or PNA (480.xx‐486.xx). We excluded patients who were coded as having in‐hospital mortality, as these patients would not be eligible for readmission, those who were transferred to a different inpatient acute‐care facility, and those with invalid RLNs. Patients were separated into 2 groups based on the day of discharge. Weekday was defined as Monday through Friday, whereas weekend was defined as Saturday and Sunday. The Charlson Comorbidity Index was calculated based on POA comorbidities.

Demographic data, hospital variables, and readmission rates were directly compared for patients discharged on a weekend compared to weekday after admission for AMI, CHF, or PNA. Hospital readmission was defined as the first inpatient hospitalization for any reason at either 30 or 90 days following discharge from an index acute‐care hospitalization. Hospital identification codes were used to determine whether the readmission occurred at the index (discharging) hospital or to a different facility. The principal diagnosis for the subsequent admission was assessed to identify the most common reasons for readmission.

The [2] test and Student t test were used to compare mean values between the 2 groups when appropriate, with statistical significance set as P<0.05. Univariate and multivariable logistic regression models were built to estimate the odds of hospital readmission based on weekend versus weekday discharge after controlling for age, gender, race, Charlson Comorbidity Index, discharge disposition, payer status, length of stay, presence of complication, and admission type. All statistical analyses were 2‐tailed and performed using SAS 9.3 for windows (SAS Institute Inc., Cary, NC). The odds ratio (OR) was considered significant when it was not equal to 1, the 95% confidence interval (CI) did not include 1, and the P value was less than 0.05.

RESULTS

Patient Characteristics

There were 266,519 patients hospitalized with a principal diagnosis of AMI, CHF, or PNA in California during 2012 and met all inclusion criteria. The cohort consisted of 77,853 (29.2%) with AMI, 91,327 (34.3%) with CHF, and 97,339 (36.5%) with PNA. A total of 60,097 (22.5%) patients were discharged on the weekend compared to 206,422 (77.5%) on a weekday, which was similar across diagnosis groups. Differences in gender, age, race, Charlson comorbidity score, insurance status, type of admission, or occurrence of complications between patients who were discharged on the weekend versus weekday are listed in Table 1. Patients discharged on a weekend had a shorter average length of stay (LOS) (AMI: 4.05.6 days vs 4.67.7 days; CHF: 5.19.3 vs 6.034.1; PNA: 5.011.7 vs 5.710.7). A higher proportion of these patients were discharged to home (AMI: 67.1% vs 63.8%; CHF: 53.3% vs 49.4%; PNA: 57.0% vs 52.9%), whereas a smaller proportion were discharged to an SNF (AMI: 7.0% vs 9.6%; CHF: 11.2% vs 15.9%; PNA: 12.8% vs 17.8%).

Cohort Demographics
 AMICHFPNA
WeekendWeekdayWeekendWeekdayWeekendWeekday
  • NOTE: All numbers are expressed in percentage of entire cohort unless otherwise stated. Abbreviations: AMI, acute myocardial infarction; API, Asian/Pacific Islander; CHF, congestive heart failure; DVT/PE, deep vein thrombosis and/or pulmonary embolism; MI, myocardial infarction; PNA, pneumonia; SD, standard deviation.

No. (%)18,061 (23.2)59,792 (76.8)20,487 (22.4)70,840 (77.6)21,549 (22.1)75,790 (77.9)
Age, y      
0444.74.54.54.19.48.6
455413.113.08.58.39.89.9
556422.622.414.314.614.914.9
657422.522.719.218.718.318.0
758421.421.426.426.324.124.0
85+15.616.027.228.023.524.5
Mean (SD)68.5 (14.3)68.7 (14.3)73.3 (15.1)3.6 (15.0)70.0 (17.6)70.5 (17.4)
Sex      
Male62.061.751.751.447.947.0
Female38.038.348.348.652.152.1
Race      
White63.562.958.758.563.062.4
Black6.97.312.012.17.78.0
Hispanic19.520.020.320.620.420.7
API10.09.79.08.88.88.9
Charlson Comorbidity Index      
030.730.19.49.523.022.2
125.124.919.519.825.726.4
214.915.220.420.317.317.4
329.229.850.850.434.034.1
Mean (SD)2.1 (2.2)2.1 (2.2)3.0 (2.3)3.0 (2.3)2.4 (2.6)2.4 (2.5)
Payer status      
Private25.425.111.310.715.714.4
Medicare57.657.972.773.167.168.1
Medicaid8.08.010.010.611.511.8
No insurance4.24.02.72.32.62.5
Unknown4.84.93.33.33.23.2
Complication      
Urinary tract infection6.06.810.310.810.211.0
Acute MI6.76.92.72.61.21.2
DVT/PE0.020.020.010.010.030.03
Pneumonia0.060.050.090.080.10.1
Hemorrhage1.71.71.51.51.21.1
Sepsis3.53.66.26.07.47.6
Mean length of stay (SD)4.0 (5.6)4.6 (7.7)5.1 (9.3)6.0 (34.1)5.0 (11.7)5.7 (10.7)
Disposition      
Home67.163.853.349.457.052.9
Acute rehabilitation1.93.20.70.90.50.7
Skilled nursing facility7.09.611.215.912.817.8
Residential facility0.40.50.91.01.11.4
Other23.623.033.932.828.627.2
Admission type      
Elective8.910.17.99.17.17.6
Unplanned91.089.992.190.992.992.3

Rate, Reason, and Location of Readmission

Table 2 shows overall rates of readmission. Among all patients, there were no significant differences in the unadjusted readmission rates for patients being discharged on a weekend versus weekday at either 30 days (16.7% vs 17.0%, P=0.14) or 90 days (26.9% vs 27.5%, P=0.05) (Table 2). Unadjusted 30‐day readmission rates were similar between the 2 groups for AMI (21.9% vs 21.9%, P=0.94) and PNA (12.1% vs 12.4%, P=0.28), whereas they were higher for weekday discharges in CHF (15.4% vs 16.0%, P=0.04). Similar results were seen for 90‐day readmission rates. To elucidate the impact of discharge disposition, a subset analysis was performed based on day of discharge and disposition (Figure 1). There was no difference in rates of readmission among patients discharged home on a weekend versus weekday (AMI: 21.3% vs 21.1%, P=0.78; CHF: 12.2% vs 12.6%, P=0.29; PNA: 8.3% vs 8.6%, P=0.29).

Figure 1
Thirty‐day readmission rate for AMI, CHF, and PNA based on discharge disposition.
Abbreviations: AMI, acute myocardial infarction; CHF, congestive heart failure; PNA, pneumonia; SNF, skilled nursing facility.
Unadjusted Readmission Rates Based on Day of Discharge
 AMICHFPNA
WeekendWeekdayP ValueWeekendWeekdayP ValueWeekendWeekdayP Value
  • NOTE: Abbreviations: AMI, acute myocardial infarction; CHF, congestive heart failure; PNA, pneumonia.

30‐day readmission (%)3,954 (21.9)13,106 (21.9)0.943,162 (15.4)11,366 (16.0)0.042,608 (12.1)9,380 (12.4)0.28
90‐day readmission (%)5,253 (29.1)17,344 (29.0)0.845,994 (29.3)21,355 (30.2)0.0084,698 (21.8)16,910 (22.3)0.11

The reason for hospital readmission was most frequently related to the principal diagnosis. Among patients discharged after hospitalization for AMI, 45.3% of readmissions had a principal diagnosis of AMI, whereas 13.9% listed readmission for angina or coronary artery disease. Of CHF discharges, at least 26.7% of readmissions were for CHF. PNA was the principal diagnosis in 19.8% of readmissions after admission for PNA. A significant proportion of patients (AMI: 64.8%, CHF: 35.0%, PNA: 32.9%) were readmitted to a different hospital than the discharging hospital.

Predictors of Readmission

On univariate logistic regression, discharge on a weekend was not associated with hospital readmission for patients admitted with AMI (OR: 1.0, 95% CI: 0.96‐1.04) or PNA (OR: 0.97, 95% CI: 0.93‐1.02) but was inversely associated for CHF (OR: 0.96, 95% CI: 0.91‐1.0). In multivariable models, weekend discharge was not associated with increased risk of readmission for any diagnosis (AMI [OR: 1.02, 95% CI: 0.98‐1.07], CHF [OR: 0.99, 95% CI: 0.95‐1.03], or PNA [OR: 1.02, 95% CI: 0.98‐1.07]; Table 3).

Logistic Regression Analysis of Variables Predicting 30‐Day Readmission
 AMICHFPNA
Univariate OR (95% CI)Multivariable OR (95% CI)Univariate OR (95% CI)Multivariate OR (95% CI)Univariate OR (95% CI)Multivariate OR (95% CI)
  • NOTE: Abbreviations: AMI, acute myocardial infarction; API, Asian/Pacific Islander; CHF, congestive heart failure; CI, confidence interval; OR, odds ratio; PNA, pneumonia; SNF, skilled nursing facility. *Coefficient should be interpreted as odds ratio per doubling length of stay.

Weekend discharge1 (0.96‐1.04)1.02 (0.98‐1.06)0.96 (0.91‐1)0.99 (0.94‐1.03)0.97 (0.93‐1.02)1.02 (0.98‐1.07)
Age, y      
044      
45541.02 (0.92‐1.12)0.96 (0.87‐1.07)1.04 (0.93‐1.16)1.00 (0.89‐1.11)1.08 (0.98‐1.19)0.93 (0.84‐1.03)
55641.11 (1.02‐1.22)1.00 (0.91‐1.10)1.11 (1.01‐1.23)0.97 (0.88‐1.08)1.23 (1.13‐1.34)0.94 (0.86‐1.03)
65741.31 (1.19‐1.43)1.04 (0.94‐1.15)1.1 (1‐1.22)0.90 (0.81‐1.01)1.29 (1.19‐1.41)0.87 (0.79‐0.96)
75841.29 (1.18‐1.41)0.94 (0.85‐1.05)1.06 (0.97‐1.17)0.84 (0.75‐0.93)1.37 (1.27‐1.49)0.87 (0.79‐0.95)
85+1.03 (0.94‐1.13)0.72 (0.64‐0.81)0.98 (0.89‐1.08)0.76 (0.68‐0.84)1.31 (1.2‐1.41)0.78 (0.71‐0.86)
Gender      
Female      
Male1 (0.97‐1.04)1.1 (1.05‐1.14)1.06 (1.02‐1.1)1.08 (1.04‐1.12)1.13 (1.09‐1.18)1.15 (1.10‐1.19)
Race      
White      
Black1.17 (1.1‐1.25)1.12 (1.05‐1.20)1.06 (1‐1.12)1.03 (0.97‐1.09)1.11 (1.04‐1.19)1.07 (0.99‐1.15)
Hispanic1.11 (1.06‐1.16)1.12 (1.06‐1.17)1.05 (1‐1.1)1.04 (1.00‐1.10)0.93 (0.89‐0.98)0.95 (0.90‐1.00)
API1.14 (1.07‐1.2)1.09 (1.03‐1.16)1.01 (0.95‐1.08)1.00 (0.94‐1.07)0.97 (0.91‐1.04)0.93 (0.86‐0.99)
Charlson Comorbidity Index      
0      
11.54 (1.46‐1.62)1.40 (1.32‐1.48)1.02 (0.95‐1.1)1.0 (0.92‐1.08)1.19 (1.12‐1.26)1.11 (1.04‐1.19)
21.78 (1.69‐1.89)1.60 (1.51‐1.70)1.16 (1.08‐1.25)1.11 (1.03‐1.20)1.43 (1.34‐1.53)1.22 (1.14‐1.31)
32.07 (1.97‐2.17)1.83 (1.73‐1.93)1.41 (1.32‐1.51)1.24 (1.15‐1.32)1.79 (1.69‐1.89)1.40 (1.31‐1.48)
Payer status      
Private      
Medicare1.02 (0.98‐1.06)0.89 (0.84‐0.95)1.04 (0.98‐1.11)1.04 (0.98‐1.12)1.29 (1.22‐1.37)1.06 (0.98‐1.13)
Medicaid0.89 (0.83‐0.96)0.83 (0.77‐0.89)1.2 (1.12‐1.3)1.23 (1.13‐1.33)1.28 (1.18‐1.38)1.18 (1.09‐1.28)
No insurance0.52 (0.46‐0.58)0.60 (0.53‐0.67)0.66 (0.57‐0.76)0.79 (0.68‐0.91)0.64 (0.54‐0.75)0.73 (0.61‐0.87)
Unknown0.71 (0.65‐0.78)0.77 (0.70‐0.84)0.91 (0.81‐1.03)1.02 (0.9‐1.15)0.9 (0.79‐1.03)0.93 (0.81‐1.06)
Disposition      
Home      
Acute care0.32 (0.27‐0.37)0.35 (0.29‐0.41)1.42 (1.18‐1.71)1.2 (1.05‐1.55)2.08 (1.69‐2.56)1.64 (1.32‐2.03)
SNF1.27 (1.2‐1.34)1.18 (1.10‐1.26)1.61 (1.53‐1.7)1.54 (1.46‐1.63)1.9 (1.81‐2.01)1.61 (1.52‐1.71)
Residential facility0.89 (0.68‐1.15)0.94 (0.72‐1.24)1.31 (1.1‐1.58)1.40 (1.16‐1.69)1.61 (1.37‐1.89)1.52 (1.29‐1.80)
Other1.21 (1.16‐1.26)1.10 (1.05‐1.15)1.72 (1.66‐1.79)1.59 (1.52‐1.66)2.31 (2.21‐2.41)1.88 (1.79‐1.98)
Length of stay*1.04 (1.02‐1.05)0.89 (0.87‐0.90)1.20 (1.19‐1.22)1.09 (1.08‐1.11)1.31 (1.29‐1.32)1.13 (1.1‐1.14)
Any complication3.14 (3.02‐3.26)2.61 (2.50‐2.73)1.52 (1.46‐1.59)1.35 (1.29‐1.41)1.70 (1.62‐1.78)1.39 (1.32‐1.45)
Admission type      
Elective      
Unplanned0.28 (0.27‐0.29)0.33 (0.31‐0.34)0.56 (0.54‐0.59)0.57 (0.53‐0.6)0.39 (0.37‐0.42)0.45 (0.42‐0.48)

Increasing age, male gender, black race, greater Charlson Comorbidity Index, occurrence of any complication, and increased LOS were all associated with need for readmission on univariate analysis, though many of these associations weakened on multivariable analysis (Table 3). The effect of payer status on readmission was complex. Compared to private insurance, Medicare was associated with readmissions for patients with PNA (OR: 1.29, 95% CI: 1.22‐1.37) but not AMI (OR: 1.02, 95% CI: 0.98‐1.06) or CHF (OR: 1.04, 95% CI: 0.98‐1.11). Medicaid insurance was associated with readmission for CHF (OR: 1.20, 95% CI: 1.12‐1.30) and PNA (OR: 1.28, 95% CI: 1.18‐1.38) but appeared to be protective from readmission for AMI (OR: 0.89, 95% CI: 0.83‐0.96). Lack of insurance was associated with decreased odds of readmission for all diagnoses (P<0.05 for all models).

Models predicting 90‐day readmission rates showed similar results in all categories; therefore, the data are not shown.

DISCUSSION

We used a California statewide discharge database that linked individual patient records from all nonfederal hospitals to examine 30‐ and 90‐day hospital readmissions for CHF, AMI, and PNA. We hypothesized, but did not find, that weekend hospital discharge would be associated with higher hospital readmission rates. We did find other factors that were associated with hospital readmissions, including race, age, greater comorbidities, male gender, and discharge to an SNF. Nearly half of patients were readmitted for the same diagnosis as the initial discharge diagnosis, and nearly two‐thirds of the patients were readmitted to a hospital different from the discharging hospital.

Our study found some findings similar to prior investigations. First, the factors that predicted hospital readmission were complex and included age, race, gender, comorbidities, payer status, length of hospital stay, and the occurrence of a complication; most of these factors persisted after multivariable analysis but were not necessarily consistent across all admission diagnoses.[16, 17, 18] One finding of particular interest was the impact of insurance status. Specifically, lack of insurance was inversely associated with hospital readmission; this finding warrants further investigation. Our study is also similar to others in that we found that the most common reasons for readmission are typically related to the reason for the principal admission. Dharmarajan et al. previously studied the reason for readmission among hospitalized Medicare patients with AMI, CHF, and PNA, and found similarly high rates of identical admission diagnoses.[19] Furthermore, in our study, between 32% and 65% of 30‐day readmissions were to a hospital different than the discharging facility. Although few prior studies have had the ability to assess readmission to alternative hospitals, those who have done so in the past have found similar rates of divergence from the index facility.[20, 21]

Despite the apparent similarities to other studies, the current research question was specifically designed to investigate the weekend effect of hospital discharge. The term weekend effect refers to a phenomenon of worse clinical outcomes (eg, morbidity,[22] mortality,[6, 7] intensive care unit [ICU] readmission,[23] delays in appropriate diagnostic imaging[24, 25] and intervention,[26, 27] LOS,[28] and hospital costs[29]) for care delivered on a weekend. In a landmark study, Bell and Redelmeier demonstrated increased in‐house mortality for patients with ruptured abdominal aortic aneurysm, pulmonary embolism, or acute epiglottitis admitted through the emergency department on a weekend compared to weekday.[6] After controlling for patient variables, the association persisted, suggesting system‐related factors were contributory. Similarly, Kostis et al. showed that patients admitted to the hospital on a weekend with AMI had higher 30‐day mortality rates compared to those with weekday admission.[7] Finally, Aylin et al. demonstrated that mortality was 44% higher for patients undergoing elective surgery on a Friday and 82% higher for surgery on a weekend compared to a Monday.[30]

Despite this robust literature, fewer studies have evaluated the relationship between timing of discharge and outcomes. Much of the initial research has been focused on timing of discharge from the ICU. For example, transfer out of the ICU at night has been associated with higher in‐hospital mortality[31, 32, 33, 34, 35] as well as ICU readmission.[36, 37] Discharge from the ICU on a weekend has been associated with increased mortality in some studies[23] but not in others.[35, 38] Van Walraven and Bell were the first to investigate the impact of weekend hospital discharge on outcomes. In their analysis of all discharges from Ontario hospitals between 1990 and 2000, patients discharged on a Friday were at increased risk of death and 30‐day readmission compared to discharge on a Wednesday.[9] Beck et al. performed a similar study in pediatric patients but did not find a statistically significant effect of Friday discharge on readmission rates.[39] McAlister et al. specifically studied the effect of weekend (Saturday or Sunday) discharge on patients with CHF by analyzing discharges from Alberta, Canada hospitals between 1999 and 2009. Despite being comprised of lower‐risk patients, weekend discharge was associated with greater rates of 30‐ and 90‐day death and hospital readmission.[10] Conversely, McAlister et al. evaluated general medicine discharges from teaching hospitals in Alberta, Canada between 2009 and 2011 and found no difference in hospital readmission rates among those discharged on a weekend versus weekday.[11] The current investigation is the first to study hospitals in the United States to address this topic, an important consideration given differences in American and Canadian healthcare systems. Nevertheless, our results are similar to those of McAlister et al.,[11] who found no difference in hospital readmission rates based on day of discharge among patients with AMI, CHF, or PNA.

One potential explanation for finding a lack of correlation between weekend discharge and readmissions is that patients at higher risk for readmission are already selected toward weekday discharge. Our study found that patients discharged to an SNF, a group with higher odds of readmission, were less often discharged on a weekend. There may be other unmeasurable factors that differ between patients discharged on weekends versus weekdays. Also, factors that bias healthcare providers' decision making on timing of discharge are difficult to quantify and may differ between the 2 groups. Although our study hypothesis was driven by the perception that weekend discharges may fare poorly because of inadequate resources on the weekend, an alternative explanation for finding no association may be that current systems in place already do an effective job of discharge coordination on the weekend. Despite fears that staffing and equipment are significantly reduced during the weekend, perhaps weekend discharge resources are not the limiting factor in efforts to reduce readmissions.

Our results challenge the idea that weekend discharges predict hospital readmissions in California and argue for the relative safety of weekend discharges. Based on these findings, the routine delay in discharge of the complex medical patient until Monday for fear of discharge on a weekend does not seem warranted. Avoiding unnecessary delays in discharge should have positive effects on healthcare costs by reducing LOS. Two additional implications of our work are that single institution studies may underestimate readmission rates,[40] and that discharge to an SNF should receive special consideration in calculation of hospital‐level penalties for subsequent readmissions, as this group is associated with particularly higher risk.

There are some limitations to our study that should be acknowledged. The use of administrative data has well known limitations and the possibility of coding inaccuracy cannot be excluded.[41] Certain factors that could potentially differ between groups, such as illness severity, as well as details on the discharge process, were not available in this administrative database. In addition, elective readmissions were not excluded from the study. Also, because of the way the data were coded, a significant percentage of discharge dispositions were unknown. Finally, although morbidity and mortality have been studied in previous reports,[9, 10, 39] these data were not available for the current study, limiting the applicability of its conclusions.

CONCLUSIONS

In conclusion, among patients admitted with AMI, CHF, or PNA in California, discharge on a weekend is not associated with hospital readmission. Future studies on hospital readmissions should use a population‐based approach to accurately capture all readmissions following discharge.

Acknowledgments

Disclosure: Nothing to report.

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References
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  11. McAlister FA, Youngson E, Padwal RS, Majumdar SR. Similar outcomes among general medicine patients discharged on weekends. J Hosp Med. 2015;10(2):6974.
  12. Misky GJ, Wald HL, Coleman EA. Post‐hospitalization transitions: examining the effects of timing of primary care provider follow‐up. J Hosp Med. 2010;5(7):392397.
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  14. Cornish PL, Knowles SR, Marchesano R, et al. Unintended medication discrepancies at the time of hospital admission. Arch Intern Med. 2005;165(4):424429.
  15. Readmissions Reduction Program. August 2014. Available at: http://www.cms.gov/Medicare/Medicare‐Fee‐for‐Service‐Payment/AcuteInpatientPPS/Readmissions‐Reduction‐Program.html. Accessed October 2, 2014.
  16. Joynt KE, Orav EJ, Jha AK. Thirty‐day readmission rates for Medicare beneficiaries by race and site of care. JAMA. 2011;305(7):675681.
  17. Hasan O, Meltzer DO, Shaykevich SA, et al. Hospital readmission in general medicine patients: a prediction model. J Gen Intern Med. 2009;25(3):211219.
  18. Jencks SF, Williams MV, Coleman EA. Rehospitalizations among patients in the Medicare fee‐for‐service program. N Engl J Med. 2009;360(14):14181428.
  19. Dharmarajan K, Hsieh AF, Lin Z, et al. Diagnoses and timing of 30‐day readmissions after hospitalization for heart failure, acute myocardial infarction, or pneumonia. JAMA. 2013;309(4):355363.
  20. Yermilov I, Bentrem D, Sekeris E, et al. Readmissions following pancreaticoduodenectomy for pancreas cancer: a population‐based appraisal. Ann Surg Oncol. 2009;16(3):554561.
  21. Nasir K, Lin Z, Bueno H, et al. Is same‐hospital readmission rate a good surrogate for all‐hospital readmission rate? Med Care. 2010;48(5):477481.
  22. Worni M, Schudel IM, Østbye T, et al. Worse outcomes in patients undergoing urgent surgery for left‐sided diverticulitis admitted on weekends vs weekdays: a population‐based study of 31 832 patients. Arch Surg. 2012;147(7):649655.
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Journal of Hospital Medicine - 10(11)
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Hospital readmission, defined as an admission to a hospital within 30 days of discharge from an acute‐care hospitalization, is associated with short‐term morbidity, mortality, and medical costs.[1] In 2013, the Patient Protection and Affordable Care Act began assigning financial penalties to hospitals based on performance against benchmarks on readmission for acute myocardial infarction (AMI), pneumonia (PNA), and congestive heart failure (CHF) through its Hospital Readmission Reduction Program (HRRP).[2] In its third year, the program recently announced penalties for 2,610 hospitals that will total over $428 million.[3] Despite increased attention to this issue, few interventions have been identified that effectively reduce hospital readmissions.[4, 5]

Hospital discharge is a complex process that aims to achieve the safe transfer of care of a hospitalized patient to another setting (eg, home, skilled nursing facility [SNF]). Success depends on adequate staffing of physicians, nurses, case managers, social workers, and pharmacists; clear communication among patients and providers; and integrated coordination of care. Although much focus has been placed on the association between weekend hospital admission and increased mortality,[6, 7, 8] very little is known about the impact of weekend hospital discharge on outcomes, specifically hospital readmission rates. Furthermore, previous studies on this topic, based on Canadian data, have produced conflicting results.[9, 10, 11]

Staffing of physicians, physician extenders (eg, physician assistants or nurse practitioners), nurses, case managers, social workers, and ancillary staff (eg, physical and occupational therapists) are all typically reduced on the weekend. Patients may be cared for by covering healthcare providers. These factors may have important implications on the timeliness of discharge, accuracy of discharge instructions, safety of discharge (eg, clearance by physical therapy), and medication reconciliation, among others. Clinic offices are more likely to be closed, and therefore, some follow‐up appointments may inadvertently not be scheduled, and lack of timely postdischarge follow‐up may be associated with higher rates of readmission.[12] Reduced outpatient pharmacy availability may also cause delays in patients receiving their medications,[13] which may exacerbate failed transition to the outpatient setting due to medication noncompliance.[14]

Based on this rationale, the current study was designed to investigate the association between weekend discharge and 30‐ and 90‐ day readmissions in patients hospitalized for medical diagnoses included in Centers for Medicare and Medicaid Services' HRRP.[15] To do so, a large‐state, all‐payer discharge database with individual patient record linkage numbers (RLN) was selected to capture all readmissions, even those to a different hospital. We hypothesized that patients who are discharged on a weekend would have higher hospital readmission rates compared to those discharged on a weekday.

METHODS

Approval was obtained from both the California Committee for the Protection of Human Subjects and the Stanford University Institutional Review Board. The California Office of State Health Planning and Development (OSHPD) 2012 Patient Discharge Data (PDD) was utilized for this study. The OSHPD‐PDD contains records for all patients admitted and eventually discharged from every general, acute, nonfederal hospital within the state. Demographic variables contained in the dataset include age, gender, race, and a unique RLN (an individually assigned number based on the patient's social security number and other demographics) to associate discharged patients with subsequent hospitalizations. Clinical information collected included principal diagnosis (indication for admission), 24 additional diagnoses with an indicator as to whether or not the condition was present on admission (POA) to differentiate comorbidities from complications, and principle procedure codes. Details about the admission included date of admission and discharge, admission type (scheduled or unscheduled), expected payer/emnsurance and disposition (home, acute rehabilitation, skilled nursing facility, residential facility, other). Details about the hospital included a unique identification number to indicate the location of care for both index/discharge and subsequent readmission.

International Classification of Disease, Ninth Edition, Clinical Modification (ICD‐9‐CM) coding schema were used to identify all patients admitted with the principal diagnosis of AMI (ICD‐9‐CM code 410.xx), CHF (428.xx), or PNA (480.xx‐486.xx). We excluded patients who were coded as having in‐hospital mortality, as these patients would not be eligible for readmission, those who were transferred to a different inpatient acute‐care facility, and those with invalid RLNs. Patients were separated into 2 groups based on the day of discharge. Weekday was defined as Monday through Friday, whereas weekend was defined as Saturday and Sunday. The Charlson Comorbidity Index was calculated based on POA comorbidities.

Demographic data, hospital variables, and readmission rates were directly compared for patients discharged on a weekend compared to weekday after admission for AMI, CHF, or PNA. Hospital readmission was defined as the first inpatient hospitalization for any reason at either 30 or 90 days following discharge from an index acute‐care hospitalization. Hospital identification codes were used to determine whether the readmission occurred at the index (discharging) hospital or to a different facility. The principal diagnosis for the subsequent admission was assessed to identify the most common reasons for readmission.

The [2] test and Student t test were used to compare mean values between the 2 groups when appropriate, with statistical significance set as P<0.05. Univariate and multivariable logistic regression models were built to estimate the odds of hospital readmission based on weekend versus weekday discharge after controlling for age, gender, race, Charlson Comorbidity Index, discharge disposition, payer status, length of stay, presence of complication, and admission type. All statistical analyses were 2‐tailed and performed using SAS 9.3 for windows (SAS Institute Inc., Cary, NC). The odds ratio (OR) was considered significant when it was not equal to 1, the 95% confidence interval (CI) did not include 1, and the P value was less than 0.05.

RESULTS

Patient Characteristics

There were 266,519 patients hospitalized with a principal diagnosis of AMI, CHF, or PNA in California during 2012 and met all inclusion criteria. The cohort consisted of 77,853 (29.2%) with AMI, 91,327 (34.3%) with CHF, and 97,339 (36.5%) with PNA. A total of 60,097 (22.5%) patients were discharged on the weekend compared to 206,422 (77.5%) on a weekday, which was similar across diagnosis groups. Differences in gender, age, race, Charlson comorbidity score, insurance status, type of admission, or occurrence of complications between patients who were discharged on the weekend versus weekday are listed in Table 1. Patients discharged on a weekend had a shorter average length of stay (LOS) (AMI: 4.05.6 days vs 4.67.7 days; CHF: 5.19.3 vs 6.034.1; PNA: 5.011.7 vs 5.710.7). A higher proportion of these patients were discharged to home (AMI: 67.1% vs 63.8%; CHF: 53.3% vs 49.4%; PNA: 57.0% vs 52.9%), whereas a smaller proportion were discharged to an SNF (AMI: 7.0% vs 9.6%; CHF: 11.2% vs 15.9%; PNA: 12.8% vs 17.8%).

Cohort Demographics
 AMICHFPNA
WeekendWeekdayWeekendWeekdayWeekendWeekday
  • NOTE: All numbers are expressed in percentage of entire cohort unless otherwise stated. Abbreviations: AMI, acute myocardial infarction; API, Asian/Pacific Islander; CHF, congestive heart failure; DVT/PE, deep vein thrombosis and/or pulmonary embolism; MI, myocardial infarction; PNA, pneumonia; SD, standard deviation.

No. (%)18,061 (23.2)59,792 (76.8)20,487 (22.4)70,840 (77.6)21,549 (22.1)75,790 (77.9)
Age, y      
0444.74.54.54.19.48.6
455413.113.08.58.39.89.9
556422.622.414.314.614.914.9
657422.522.719.218.718.318.0
758421.421.426.426.324.124.0
85+15.616.027.228.023.524.5
Mean (SD)68.5 (14.3)68.7 (14.3)73.3 (15.1)3.6 (15.0)70.0 (17.6)70.5 (17.4)
Sex      
Male62.061.751.751.447.947.0
Female38.038.348.348.652.152.1
Race      
White63.562.958.758.563.062.4
Black6.97.312.012.17.78.0
Hispanic19.520.020.320.620.420.7
API10.09.79.08.88.88.9
Charlson Comorbidity Index      
030.730.19.49.523.022.2
125.124.919.519.825.726.4
214.915.220.420.317.317.4
329.229.850.850.434.034.1
Mean (SD)2.1 (2.2)2.1 (2.2)3.0 (2.3)3.0 (2.3)2.4 (2.6)2.4 (2.5)
Payer status      
Private25.425.111.310.715.714.4
Medicare57.657.972.773.167.168.1
Medicaid8.08.010.010.611.511.8
No insurance4.24.02.72.32.62.5
Unknown4.84.93.33.33.23.2
Complication      
Urinary tract infection6.06.810.310.810.211.0
Acute MI6.76.92.72.61.21.2
DVT/PE0.020.020.010.010.030.03
Pneumonia0.060.050.090.080.10.1
Hemorrhage1.71.71.51.51.21.1
Sepsis3.53.66.26.07.47.6
Mean length of stay (SD)4.0 (5.6)4.6 (7.7)5.1 (9.3)6.0 (34.1)5.0 (11.7)5.7 (10.7)
Disposition      
Home67.163.853.349.457.052.9
Acute rehabilitation1.93.20.70.90.50.7
Skilled nursing facility7.09.611.215.912.817.8
Residential facility0.40.50.91.01.11.4
Other23.623.033.932.828.627.2
Admission type      
Elective8.910.17.99.17.17.6
Unplanned91.089.992.190.992.992.3

Rate, Reason, and Location of Readmission

Table 2 shows overall rates of readmission. Among all patients, there were no significant differences in the unadjusted readmission rates for patients being discharged on a weekend versus weekday at either 30 days (16.7% vs 17.0%, P=0.14) or 90 days (26.9% vs 27.5%, P=0.05) (Table 2). Unadjusted 30‐day readmission rates were similar between the 2 groups for AMI (21.9% vs 21.9%, P=0.94) and PNA (12.1% vs 12.4%, P=0.28), whereas they were higher for weekday discharges in CHF (15.4% vs 16.0%, P=0.04). Similar results were seen for 90‐day readmission rates. To elucidate the impact of discharge disposition, a subset analysis was performed based on day of discharge and disposition (Figure 1). There was no difference in rates of readmission among patients discharged home on a weekend versus weekday (AMI: 21.3% vs 21.1%, P=0.78; CHF: 12.2% vs 12.6%, P=0.29; PNA: 8.3% vs 8.6%, P=0.29).

Figure 1
Thirty‐day readmission rate for AMI, CHF, and PNA based on discharge disposition.
Abbreviations: AMI, acute myocardial infarction; CHF, congestive heart failure; PNA, pneumonia; SNF, skilled nursing facility.
Unadjusted Readmission Rates Based on Day of Discharge
 AMICHFPNA
WeekendWeekdayP ValueWeekendWeekdayP ValueWeekendWeekdayP Value
  • NOTE: Abbreviations: AMI, acute myocardial infarction; CHF, congestive heart failure; PNA, pneumonia.

30‐day readmission (%)3,954 (21.9)13,106 (21.9)0.943,162 (15.4)11,366 (16.0)0.042,608 (12.1)9,380 (12.4)0.28
90‐day readmission (%)5,253 (29.1)17,344 (29.0)0.845,994 (29.3)21,355 (30.2)0.0084,698 (21.8)16,910 (22.3)0.11

The reason for hospital readmission was most frequently related to the principal diagnosis. Among patients discharged after hospitalization for AMI, 45.3% of readmissions had a principal diagnosis of AMI, whereas 13.9% listed readmission for angina or coronary artery disease. Of CHF discharges, at least 26.7% of readmissions were for CHF. PNA was the principal diagnosis in 19.8% of readmissions after admission for PNA. A significant proportion of patients (AMI: 64.8%, CHF: 35.0%, PNA: 32.9%) were readmitted to a different hospital than the discharging hospital.

Predictors of Readmission

On univariate logistic regression, discharge on a weekend was not associated with hospital readmission for patients admitted with AMI (OR: 1.0, 95% CI: 0.96‐1.04) or PNA (OR: 0.97, 95% CI: 0.93‐1.02) but was inversely associated for CHF (OR: 0.96, 95% CI: 0.91‐1.0). In multivariable models, weekend discharge was not associated with increased risk of readmission for any diagnosis (AMI [OR: 1.02, 95% CI: 0.98‐1.07], CHF [OR: 0.99, 95% CI: 0.95‐1.03], or PNA [OR: 1.02, 95% CI: 0.98‐1.07]; Table 3).

Logistic Regression Analysis of Variables Predicting 30‐Day Readmission
 AMICHFPNA
Univariate OR (95% CI)Multivariable OR (95% CI)Univariate OR (95% CI)Multivariate OR (95% CI)Univariate OR (95% CI)Multivariate OR (95% CI)
  • NOTE: Abbreviations: AMI, acute myocardial infarction; API, Asian/Pacific Islander; CHF, congestive heart failure; CI, confidence interval; OR, odds ratio; PNA, pneumonia; SNF, skilled nursing facility. *Coefficient should be interpreted as odds ratio per doubling length of stay.

Weekend discharge1 (0.96‐1.04)1.02 (0.98‐1.06)0.96 (0.91‐1)0.99 (0.94‐1.03)0.97 (0.93‐1.02)1.02 (0.98‐1.07)
Age, y      
044      
45541.02 (0.92‐1.12)0.96 (0.87‐1.07)1.04 (0.93‐1.16)1.00 (0.89‐1.11)1.08 (0.98‐1.19)0.93 (0.84‐1.03)
55641.11 (1.02‐1.22)1.00 (0.91‐1.10)1.11 (1.01‐1.23)0.97 (0.88‐1.08)1.23 (1.13‐1.34)0.94 (0.86‐1.03)
65741.31 (1.19‐1.43)1.04 (0.94‐1.15)1.1 (1‐1.22)0.90 (0.81‐1.01)1.29 (1.19‐1.41)0.87 (0.79‐0.96)
75841.29 (1.18‐1.41)0.94 (0.85‐1.05)1.06 (0.97‐1.17)0.84 (0.75‐0.93)1.37 (1.27‐1.49)0.87 (0.79‐0.95)
85+1.03 (0.94‐1.13)0.72 (0.64‐0.81)0.98 (0.89‐1.08)0.76 (0.68‐0.84)1.31 (1.2‐1.41)0.78 (0.71‐0.86)
Gender      
Female      
Male1 (0.97‐1.04)1.1 (1.05‐1.14)1.06 (1.02‐1.1)1.08 (1.04‐1.12)1.13 (1.09‐1.18)1.15 (1.10‐1.19)
Race      
White      
Black1.17 (1.1‐1.25)1.12 (1.05‐1.20)1.06 (1‐1.12)1.03 (0.97‐1.09)1.11 (1.04‐1.19)1.07 (0.99‐1.15)
Hispanic1.11 (1.06‐1.16)1.12 (1.06‐1.17)1.05 (1‐1.1)1.04 (1.00‐1.10)0.93 (0.89‐0.98)0.95 (0.90‐1.00)
API1.14 (1.07‐1.2)1.09 (1.03‐1.16)1.01 (0.95‐1.08)1.00 (0.94‐1.07)0.97 (0.91‐1.04)0.93 (0.86‐0.99)
Charlson Comorbidity Index      
0      
11.54 (1.46‐1.62)1.40 (1.32‐1.48)1.02 (0.95‐1.1)1.0 (0.92‐1.08)1.19 (1.12‐1.26)1.11 (1.04‐1.19)
21.78 (1.69‐1.89)1.60 (1.51‐1.70)1.16 (1.08‐1.25)1.11 (1.03‐1.20)1.43 (1.34‐1.53)1.22 (1.14‐1.31)
32.07 (1.97‐2.17)1.83 (1.73‐1.93)1.41 (1.32‐1.51)1.24 (1.15‐1.32)1.79 (1.69‐1.89)1.40 (1.31‐1.48)
Payer status      
Private      
Medicare1.02 (0.98‐1.06)0.89 (0.84‐0.95)1.04 (0.98‐1.11)1.04 (0.98‐1.12)1.29 (1.22‐1.37)1.06 (0.98‐1.13)
Medicaid0.89 (0.83‐0.96)0.83 (0.77‐0.89)1.2 (1.12‐1.3)1.23 (1.13‐1.33)1.28 (1.18‐1.38)1.18 (1.09‐1.28)
No insurance0.52 (0.46‐0.58)0.60 (0.53‐0.67)0.66 (0.57‐0.76)0.79 (0.68‐0.91)0.64 (0.54‐0.75)0.73 (0.61‐0.87)
Unknown0.71 (0.65‐0.78)0.77 (0.70‐0.84)0.91 (0.81‐1.03)1.02 (0.9‐1.15)0.9 (0.79‐1.03)0.93 (0.81‐1.06)
Disposition      
Home      
Acute care0.32 (0.27‐0.37)0.35 (0.29‐0.41)1.42 (1.18‐1.71)1.2 (1.05‐1.55)2.08 (1.69‐2.56)1.64 (1.32‐2.03)
SNF1.27 (1.2‐1.34)1.18 (1.10‐1.26)1.61 (1.53‐1.7)1.54 (1.46‐1.63)1.9 (1.81‐2.01)1.61 (1.52‐1.71)
Residential facility0.89 (0.68‐1.15)0.94 (0.72‐1.24)1.31 (1.1‐1.58)1.40 (1.16‐1.69)1.61 (1.37‐1.89)1.52 (1.29‐1.80)
Other1.21 (1.16‐1.26)1.10 (1.05‐1.15)1.72 (1.66‐1.79)1.59 (1.52‐1.66)2.31 (2.21‐2.41)1.88 (1.79‐1.98)
Length of stay*1.04 (1.02‐1.05)0.89 (0.87‐0.90)1.20 (1.19‐1.22)1.09 (1.08‐1.11)1.31 (1.29‐1.32)1.13 (1.1‐1.14)
Any complication3.14 (3.02‐3.26)2.61 (2.50‐2.73)1.52 (1.46‐1.59)1.35 (1.29‐1.41)1.70 (1.62‐1.78)1.39 (1.32‐1.45)
Admission type      
Elective      
Unplanned0.28 (0.27‐0.29)0.33 (0.31‐0.34)0.56 (0.54‐0.59)0.57 (0.53‐0.6)0.39 (0.37‐0.42)0.45 (0.42‐0.48)

Increasing age, male gender, black race, greater Charlson Comorbidity Index, occurrence of any complication, and increased LOS were all associated with need for readmission on univariate analysis, though many of these associations weakened on multivariable analysis (Table 3). The effect of payer status on readmission was complex. Compared to private insurance, Medicare was associated with readmissions for patients with PNA (OR: 1.29, 95% CI: 1.22‐1.37) but not AMI (OR: 1.02, 95% CI: 0.98‐1.06) or CHF (OR: 1.04, 95% CI: 0.98‐1.11). Medicaid insurance was associated with readmission for CHF (OR: 1.20, 95% CI: 1.12‐1.30) and PNA (OR: 1.28, 95% CI: 1.18‐1.38) but appeared to be protective from readmission for AMI (OR: 0.89, 95% CI: 0.83‐0.96). Lack of insurance was associated with decreased odds of readmission for all diagnoses (P<0.05 for all models).

Models predicting 90‐day readmission rates showed similar results in all categories; therefore, the data are not shown.

DISCUSSION

We used a California statewide discharge database that linked individual patient records from all nonfederal hospitals to examine 30‐ and 90‐day hospital readmissions for CHF, AMI, and PNA. We hypothesized, but did not find, that weekend hospital discharge would be associated with higher hospital readmission rates. We did find other factors that were associated with hospital readmissions, including race, age, greater comorbidities, male gender, and discharge to an SNF. Nearly half of patients were readmitted for the same diagnosis as the initial discharge diagnosis, and nearly two‐thirds of the patients were readmitted to a hospital different from the discharging hospital.

Our study found some findings similar to prior investigations. First, the factors that predicted hospital readmission were complex and included age, race, gender, comorbidities, payer status, length of hospital stay, and the occurrence of a complication; most of these factors persisted after multivariable analysis but were not necessarily consistent across all admission diagnoses.[16, 17, 18] One finding of particular interest was the impact of insurance status. Specifically, lack of insurance was inversely associated with hospital readmission; this finding warrants further investigation. Our study is also similar to others in that we found that the most common reasons for readmission are typically related to the reason for the principal admission. Dharmarajan et al. previously studied the reason for readmission among hospitalized Medicare patients with AMI, CHF, and PNA, and found similarly high rates of identical admission diagnoses.[19] Furthermore, in our study, between 32% and 65% of 30‐day readmissions were to a hospital different than the discharging facility. Although few prior studies have had the ability to assess readmission to alternative hospitals, those who have done so in the past have found similar rates of divergence from the index facility.[20, 21]

Despite the apparent similarities to other studies, the current research question was specifically designed to investigate the weekend effect of hospital discharge. The term weekend effect refers to a phenomenon of worse clinical outcomes (eg, morbidity,[22] mortality,[6, 7] intensive care unit [ICU] readmission,[23] delays in appropriate diagnostic imaging[24, 25] and intervention,[26, 27] LOS,[28] and hospital costs[29]) for care delivered on a weekend. In a landmark study, Bell and Redelmeier demonstrated increased in‐house mortality for patients with ruptured abdominal aortic aneurysm, pulmonary embolism, or acute epiglottitis admitted through the emergency department on a weekend compared to weekday.[6] After controlling for patient variables, the association persisted, suggesting system‐related factors were contributory. Similarly, Kostis et al. showed that patients admitted to the hospital on a weekend with AMI had higher 30‐day mortality rates compared to those with weekday admission.[7] Finally, Aylin et al. demonstrated that mortality was 44% higher for patients undergoing elective surgery on a Friday and 82% higher for surgery on a weekend compared to a Monday.[30]

Despite this robust literature, fewer studies have evaluated the relationship between timing of discharge and outcomes. Much of the initial research has been focused on timing of discharge from the ICU. For example, transfer out of the ICU at night has been associated with higher in‐hospital mortality[31, 32, 33, 34, 35] as well as ICU readmission.[36, 37] Discharge from the ICU on a weekend has been associated with increased mortality in some studies[23] but not in others.[35, 38] Van Walraven and Bell were the first to investigate the impact of weekend hospital discharge on outcomes. In their analysis of all discharges from Ontario hospitals between 1990 and 2000, patients discharged on a Friday were at increased risk of death and 30‐day readmission compared to discharge on a Wednesday.[9] Beck et al. performed a similar study in pediatric patients but did not find a statistically significant effect of Friday discharge on readmission rates.[39] McAlister et al. specifically studied the effect of weekend (Saturday or Sunday) discharge on patients with CHF by analyzing discharges from Alberta, Canada hospitals between 1999 and 2009. Despite being comprised of lower‐risk patients, weekend discharge was associated with greater rates of 30‐ and 90‐day death and hospital readmission.[10] Conversely, McAlister et al. evaluated general medicine discharges from teaching hospitals in Alberta, Canada between 2009 and 2011 and found no difference in hospital readmission rates among those discharged on a weekend versus weekday.[11] The current investigation is the first to study hospitals in the United States to address this topic, an important consideration given differences in American and Canadian healthcare systems. Nevertheless, our results are similar to those of McAlister et al.,[11] who found no difference in hospital readmission rates based on day of discharge among patients with AMI, CHF, or PNA.

One potential explanation for finding a lack of correlation between weekend discharge and readmissions is that patients at higher risk for readmission are already selected toward weekday discharge. Our study found that patients discharged to an SNF, a group with higher odds of readmission, were less often discharged on a weekend. There may be other unmeasurable factors that differ between patients discharged on weekends versus weekdays. Also, factors that bias healthcare providers' decision making on timing of discharge are difficult to quantify and may differ between the 2 groups. Although our study hypothesis was driven by the perception that weekend discharges may fare poorly because of inadequate resources on the weekend, an alternative explanation for finding no association may be that current systems in place already do an effective job of discharge coordination on the weekend. Despite fears that staffing and equipment are significantly reduced during the weekend, perhaps weekend discharge resources are not the limiting factor in efforts to reduce readmissions.

Our results challenge the idea that weekend discharges predict hospital readmissions in California and argue for the relative safety of weekend discharges. Based on these findings, the routine delay in discharge of the complex medical patient until Monday for fear of discharge on a weekend does not seem warranted. Avoiding unnecessary delays in discharge should have positive effects on healthcare costs by reducing LOS. Two additional implications of our work are that single institution studies may underestimate readmission rates,[40] and that discharge to an SNF should receive special consideration in calculation of hospital‐level penalties for subsequent readmissions, as this group is associated with particularly higher risk.

There are some limitations to our study that should be acknowledged. The use of administrative data has well known limitations and the possibility of coding inaccuracy cannot be excluded.[41] Certain factors that could potentially differ between groups, such as illness severity, as well as details on the discharge process, were not available in this administrative database. In addition, elective readmissions were not excluded from the study. Also, because of the way the data were coded, a significant percentage of discharge dispositions were unknown. Finally, although morbidity and mortality have been studied in previous reports,[9, 10, 39] these data were not available for the current study, limiting the applicability of its conclusions.

CONCLUSIONS

In conclusion, among patients admitted with AMI, CHF, or PNA in California, discharge on a weekend is not associated with hospital readmission. Future studies on hospital readmissions should use a population‐based approach to accurately capture all readmissions following discharge.

Acknowledgments

Disclosure: Nothing to report.

Hospital readmission, defined as an admission to a hospital within 30 days of discharge from an acute‐care hospitalization, is associated with short‐term morbidity, mortality, and medical costs.[1] In 2013, the Patient Protection and Affordable Care Act began assigning financial penalties to hospitals based on performance against benchmarks on readmission for acute myocardial infarction (AMI), pneumonia (PNA), and congestive heart failure (CHF) through its Hospital Readmission Reduction Program (HRRP).[2] In its third year, the program recently announced penalties for 2,610 hospitals that will total over $428 million.[3] Despite increased attention to this issue, few interventions have been identified that effectively reduce hospital readmissions.[4, 5]

Hospital discharge is a complex process that aims to achieve the safe transfer of care of a hospitalized patient to another setting (eg, home, skilled nursing facility [SNF]). Success depends on adequate staffing of physicians, nurses, case managers, social workers, and pharmacists; clear communication among patients and providers; and integrated coordination of care. Although much focus has been placed on the association between weekend hospital admission and increased mortality,[6, 7, 8] very little is known about the impact of weekend hospital discharge on outcomes, specifically hospital readmission rates. Furthermore, previous studies on this topic, based on Canadian data, have produced conflicting results.[9, 10, 11]

Staffing of physicians, physician extenders (eg, physician assistants or nurse practitioners), nurses, case managers, social workers, and ancillary staff (eg, physical and occupational therapists) are all typically reduced on the weekend. Patients may be cared for by covering healthcare providers. These factors may have important implications on the timeliness of discharge, accuracy of discharge instructions, safety of discharge (eg, clearance by physical therapy), and medication reconciliation, among others. Clinic offices are more likely to be closed, and therefore, some follow‐up appointments may inadvertently not be scheduled, and lack of timely postdischarge follow‐up may be associated with higher rates of readmission.[12] Reduced outpatient pharmacy availability may also cause delays in patients receiving their medications,[13] which may exacerbate failed transition to the outpatient setting due to medication noncompliance.[14]

Based on this rationale, the current study was designed to investigate the association between weekend discharge and 30‐ and 90‐ day readmissions in patients hospitalized for medical diagnoses included in Centers for Medicare and Medicaid Services' HRRP.[15] To do so, a large‐state, all‐payer discharge database with individual patient record linkage numbers (RLN) was selected to capture all readmissions, even those to a different hospital. We hypothesized that patients who are discharged on a weekend would have higher hospital readmission rates compared to those discharged on a weekday.

METHODS

Approval was obtained from both the California Committee for the Protection of Human Subjects and the Stanford University Institutional Review Board. The California Office of State Health Planning and Development (OSHPD) 2012 Patient Discharge Data (PDD) was utilized for this study. The OSHPD‐PDD contains records for all patients admitted and eventually discharged from every general, acute, nonfederal hospital within the state. Demographic variables contained in the dataset include age, gender, race, and a unique RLN (an individually assigned number based on the patient's social security number and other demographics) to associate discharged patients with subsequent hospitalizations. Clinical information collected included principal diagnosis (indication for admission), 24 additional diagnoses with an indicator as to whether or not the condition was present on admission (POA) to differentiate comorbidities from complications, and principle procedure codes. Details about the admission included date of admission and discharge, admission type (scheduled or unscheduled), expected payer/emnsurance and disposition (home, acute rehabilitation, skilled nursing facility, residential facility, other). Details about the hospital included a unique identification number to indicate the location of care for both index/discharge and subsequent readmission.

International Classification of Disease, Ninth Edition, Clinical Modification (ICD‐9‐CM) coding schema were used to identify all patients admitted with the principal diagnosis of AMI (ICD‐9‐CM code 410.xx), CHF (428.xx), or PNA (480.xx‐486.xx). We excluded patients who were coded as having in‐hospital mortality, as these patients would not be eligible for readmission, those who were transferred to a different inpatient acute‐care facility, and those with invalid RLNs. Patients were separated into 2 groups based on the day of discharge. Weekday was defined as Monday through Friday, whereas weekend was defined as Saturday and Sunday. The Charlson Comorbidity Index was calculated based on POA comorbidities.

Demographic data, hospital variables, and readmission rates were directly compared for patients discharged on a weekend compared to weekday after admission for AMI, CHF, or PNA. Hospital readmission was defined as the first inpatient hospitalization for any reason at either 30 or 90 days following discharge from an index acute‐care hospitalization. Hospital identification codes were used to determine whether the readmission occurred at the index (discharging) hospital or to a different facility. The principal diagnosis for the subsequent admission was assessed to identify the most common reasons for readmission.

The [2] test and Student t test were used to compare mean values between the 2 groups when appropriate, with statistical significance set as P<0.05. Univariate and multivariable logistic regression models were built to estimate the odds of hospital readmission based on weekend versus weekday discharge after controlling for age, gender, race, Charlson Comorbidity Index, discharge disposition, payer status, length of stay, presence of complication, and admission type. All statistical analyses were 2‐tailed and performed using SAS 9.3 for windows (SAS Institute Inc., Cary, NC). The odds ratio (OR) was considered significant when it was not equal to 1, the 95% confidence interval (CI) did not include 1, and the P value was less than 0.05.

RESULTS

Patient Characteristics

There were 266,519 patients hospitalized with a principal diagnosis of AMI, CHF, or PNA in California during 2012 and met all inclusion criteria. The cohort consisted of 77,853 (29.2%) with AMI, 91,327 (34.3%) with CHF, and 97,339 (36.5%) with PNA. A total of 60,097 (22.5%) patients were discharged on the weekend compared to 206,422 (77.5%) on a weekday, which was similar across diagnosis groups. Differences in gender, age, race, Charlson comorbidity score, insurance status, type of admission, or occurrence of complications between patients who were discharged on the weekend versus weekday are listed in Table 1. Patients discharged on a weekend had a shorter average length of stay (LOS) (AMI: 4.05.6 days vs 4.67.7 days; CHF: 5.19.3 vs 6.034.1; PNA: 5.011.7 vs 5.710.7). A higher proportion of these patients were discharged to home (AMI: 67.1% vs 63.8%; CHF: 53.3% vs 49.4%; PNA: 57.0% vs 52.9%), whereas a smaller proportion were discharged to an SNF (AMI: 7.0% vs 9.6%; CHF: 11.2% vs 15.9%; PNA: 12.8% vs 17.8%).

Cohort Demographics
 AMICHFPNA
WeekendWeekdayWeekendWeekdayWeekendWeekday
  • NOTE: All numbers are expressed in percentage of entire cohort unless otherwise stated. Abbreviations: AMI, acute myocardial infarction; API, Asian/Pacific Islander; CHF, congestive heart failure; DVT/PE, deep vein thrombosis and/or pulmonary embolism; MI, myocardial infarction; PNA, pneumonia; SD, standard deviation.

No. (%)18,061 (23.2)59,792 (76.8)20,487 (22.4)70,840 (77.6)21,549 (22.1)75,790 (77.9)
Age, y      
0444.74.54.54.19.48.6
455413.113.08.58.39.89.9
556422.622.414.314.614.914.9
657422.522.719.218.718.318.0
758421.421.426.426.324.124.0
85+15.616.027.228.023.524.5
Mean (SD)68.5 (14.3)68.7 (14.3)73.3 (15.1)3.6 (15.0)70.0 (17.6)70.5 (17.4)
Sex      
Male62.061.751.751.447.947.0
Female38.038.348.348.652.152.1
Race      
White63.562.958.758.563.062.4
Black6.97.312.012.17.78.0
Hispanic19.520.020.320.620.420.7
API10.09.79.08.88.88.9
Charlson Comorbidity Index      
030.730.19.49.523.022.2
125.124.919.519.825.726.4
214.915.220.420.317.317.4
329.229.850.850.434.034.1
Mean (SD)2.1 (2.2)2.1 (2.2)3.0 (2.3)3.0 (2.3)2.4 (2.6)2.4 (2.5)
Payer status      
Private25.425.111.310.715.714.4
Medicare57.657.972.773.167.168.1
Medicaid8.08.010.010.611.511.8
No insurance4.24.02.72.32.62.5
Unknown4.84.93.33.33.23.2
Complication      
Urinary tract infection6.06.810.310.810.211.0
Acute MI6.76.92.72.61.21.2
DVT/PE0.020.020.010.010.030.03
Pneumonia0.060.050.090.080.10.1
Hemorrhage1.71.71.51.51.21.1
Sepsis3.53.66.26.07.47.6
Mean length of stay (SD)4.0 (5.6)4.6 (7.7)5.1 (9.3)6.0 (34.1)5.0 (11.7)5.7 (10.7)
Disposition      
Home67.163.853.349.457.052.9
Acute rehabilitation1.93.20.70.90.50.7
Skilled nursing facility7.09.611.215.912.817.8
Residential facility0.40.50.91.01.11.4
Other23.623.033.932.828.627.2
Admission type      
Elective8.910.17.99.17.17.6
Unplanned91.089.992.190.992.992.3

Rate, Reason, and Location of Readmission

Table 2 shows overall rates of readmission. Among all patients, there were no significant differences in the unadjusted readmission rates for patients being discharged on a weekend versus weekday at either 30 days (16.7% vs 17.0%, P=0.14) or 90 days (26.9% vs 27.5%, P=0.05) (Table 2). Unadjusted 30‐day readmission rates were similar between the 2 groups for AMI (21.9% vs 21.9%, P=0.94) and PNA (12.1% vs 12.4%, P=0.28), whereas they were higher for weekday discharges in CHF (15.4% vs 16.0%, P=0.04). Similar results were seen for 90‐day readmission rates. To elucidate the impact of discharge disposition, a subset analysis was performed based on day of discharge and disposition (Figure 1). There was no difference in rates of readmission among patients discharged home on a weekend versus weekday (AMI: 21.3% vs 21.1%, P=0.78; CHF: 12.2% vs 12.6%, P=0.29; PNA: 8.3% vs 8.6%, P=0.29).

Figure 1
Thirty‐day readmission rate for AMI, CHF, and PNA based on discharge disposition.
Abbreviations: AMI, acute myocardial infarction; CHF, congestive heart failure; PNA, pneumonia; SNF, skilled nursing facility.
Unadjusted Readmission Rates Based on Day of Discharge
 AMICHFPNA
WeekendWeekdayP ValueWeekendWeekdayP ValueWeekendWeekdayP Value
  • NOTE: Abbreviations: AMI, acute myocardial infarction; CHF, congestive heart failure; PNA, pneumonia.

30‐day readmission (%)3,954 (21.9)13,106 (21.9)0.943,162 (15.4)11,366 (16.0)0.042,608 (12.1)9,380 (12.4)0.28
90‐day readmission (%)5,253 (29.1)17,344 (29.0)0.845,994 (29.3)21,355 (30.2)0.0084,698 (21.8)16,910 (22.3)0.11

The reason for hospital readmission was most frequently related to the principal diagnosis. Among patients discharged after hospitalization for AMI, 45.3% of readmissions had a principal diagnosis of AMI, whereas 13.9% listed readmission for angina or coronary artery disease. Of CHF discharges, at least 26.7% of readmissions were for CHF. PNA was the principal diagnosis in 19.8% of readmissions after admission for PNA. A significant proportion of patients (AMI: 64.8%, CHF: 35.0%, PNA: 32.9%) were readmitted to a different hospital than the discharging hospital.

Predictors of Readmission

On univariate logistic regression, discharge on a weekend was not associated with hospital readmission for patients admitted with AMI (OR: 1.0, 95% CI: 0.96‐1.04) or PNA (OR: 0.97, 95% CI: 0.93‐1.02) but was inversely associated for CHF (OR: 0.96, 95% CI: 0.91‐1.0). In multivariable models, weekend discharge was not associated with increased risk of readmission for any diagnosis (AMI [OR: 1.02, 95% CI: 0.98‐1.07], CHF [OR: 0.99, 95% CI: 0.95‐1.03], or PNA [OR: 1.02, 95% CI: 0.98‐1.07]; Table 3).

Logistic Regression Analysis of Variables Predicting 30‐Day Readmission
 AMICHFPNA
Univariate OR (95% CI)Multivariable OR (95% CI)Univariate OR (95% CI)Multivariate OR (95% CI)Univariate OR (95% CI)Multivariate OR (95% CI)
  • NOTE: Abbreviations: AMI, acute myocardial infarction; API, Asian/Pacific Islander; CHF, congestive heart failure; CI, confidence interval; OR, odds ratio; PNA, pneumonia; SNF, skilled nursing facility. *Coefficient should be interpreted as odds ratio per doubling length of stay.

Weekend discharge1 (0.96‐1.04)1.02 (0.98‐1.06)0.96 (0.91‐1)0.99 (0.94‐1.03)0.97 (0.93‐1.02)1.02 (0.98‐1.07)
Age, y      
044      
45541.02 (0.92‐1.12)0.96 (0.87‐1.07)1.04 (0.93‐1.16)1.00 (0.89‐1.11)1.08 (0.98‐1.19)0.93 (0.84‐1.03)
55641.11 (1.02‐1.22)1.00 (0.91‐1.10)1.11 (1.01‐1.23)0.97 (0.88‐1.08)1.23 (1.13‐1.34)0.94 (0.86‐1.03)
65741.31 (1.19‐1.43)1.04 (0.94‐1.15)1.1 (1‐1.22)0.90 (0.81‐1.01)1.29 (1.19‐1.41)0.87 (0.79‐0.96)
75841.29 (1.18‐1.41)0.94 (0.85‐1.05)1.06 (0.97‐1.17)0.84 (0.75‐0.93)1.37 (1.27‐1.49)0.87 (0.79‐0.95)
85+1.03 (0.94‐1.13)0.72 (0.64‐0.81)0.98 (0.89‐1.08)0.76 (0.68‐0.84)1.31 (1.2‐1.41)0.78 (0.71‐0.86)
Gender      
Female      
Male1 (0.97‐1.04)1.1 (1.05‐1.14)1.06 (1.02‐1.1)1.08 (1.04‐1.12)1.13 (1.09‐1.18)1.15 (1.10‐1.19)
Race      
White      
Black1.17 (1.1‐1.25)1.12 (1.05‐1.20)1.06 (1‐1.12)1.03 (0.97‐1.09)1.11 (1.04‐1.19)1.07 (0.99‐1.15)
Hispanic1.11 (1.06‐1.16)1.12 (1.06‐1.17)1.05 (1‐1.1)1.04 (1.00‐1.10)0.93 (0.89‐0.98)0.95 (0.90‐1.00)
API1.14 (1.07‐1.2)1.09 (1.03‐1.16)1.01 (0.95‐1.08)1.00 (0.94‐1.07)0.97 (0.91‐1.04)0.93 (0.86‐0.99)
Charlson Comorbidity Index      
0      
11.54 (1.46‐1.62)1.40 (1.32‐1.48)1.02 (0.95‐1.1)1.0 (0.92‐1.08)1.19 (1.12‐1.26)1.11 (1.04‐1.19)
21.78 (1.69‐1.89)1.60 (1.51‐1.70)1.16 (1.08‐1.25)1.11 (1.03‐1.20)1.43 (1.34‐1.53)1.22 (1.14‐1.31)
32.07 (1.97‐2.17)1.83 (1.73‐1.93)1.41 (1.32‐1.51)1.24 (1.15‐1.32)1.79 (1.69‐1.89)1.40 (1.31‐1.48)
Payer status      
Private      
Medicare1.02 (0.98‐1.06)0.89 (0.84‐0.95)1.04 (0.98‐1.11)1.04 (0.98‐1.12)1.29 (1.22‐1.37)1.06 (0.98‐1.13)
Medicaid0.89 (0.83‐0.96)0.83 (0.77‐0.89)1.2 (1.12‐1.3)1.23 (1.13‐1.33)1.28 (1.18‐1.38)1.18 (1.09‐1.28)
No insurance0.52 (0.46‐0.58)0.60 (0.53‐0.67)0.66 (0.57‐0.76)0.79 (0.68‐0.91)0.64 (0.54‐0.75)0.73 (0.61‐0.87)
Unknown0.71 (0.65‐0.78)0.77 (0.70‐0.84)0.91 (0.81‐1.03)1.02 (0.9‐1.15)0.9 (0.79‐1.03)0.93 (0.81‐1.06)
Disposition      
Home      
Acute care0.32 (0.27‐0.37)0.35 (0.29‐0.41)1.42 (1.18‐1.71)1.2 (1.05‐1.55)2.08 (1.69‐2.56)1.64 (1.32‐2.03)
SNF1.27 (1.2‐1.34)1.18 (1.10‐1.26)1.61 (1.53‐1.7)1.54 (1.46‐1.63)1.9 (1.81‐2.01)1.61 (1.52‐1.71)
Residential facility0.89 (0.68‐1.15)0.94 (0.72‐1.24)1.31 (1.1‐1.58)1.40 (1.16‐1.69)1.61 (1.37‐1.89)1.52 (1.29‐1.80)
Other1.21 (1.16‐1.26)1.10 (1.05‐1.15)1.72 (1.66‐1.79)1.59 (1.52‐1.66)2.31 (2.21‐2.41)1.88 (1.79‐1.98)
Length of stay*1.04 (1.02‐1.05)0.89 (0.87‐0.90)1.20 (1.19‐1.22)1.09 (1.08‐1.11)1.31 (1.29‐1.32)1.13 (1.1‐1.14)
Any complication3.14 (3.02‐3.26)2.61 (2.50‐2.73)1.52 (1.46‐1.59)1.35 (1.29‐1.41)1.70 (1.62‐1.78)1.39 (1.32‐1.45)
Admission type      
Elective      
Unplanned0.28 (0.27‐0.29)0.33 (0.31‐0.34)0.56 (0.54‐0.59)0.57 (0.53‐0.6)0.39 (0.37‐0.42)0.45 (0.42‐0.48)

Increasing age, male gender, black race, greater Charlson Comorbidity Index, occurrence of any complication, and increased LOS were all associated with need for readmission on univariate analysis, though many of these associations weakened on multivariable analysis (Table 3). The effect of payer status on readmission was complex. Compared to private insurance, Medicare was associated with readmissions for patients with PNA (OR: 1.29, 95% CI: 1.22‐1.37) but not AMI (OR: 1.02, 95% CI: 0.98‐1.06) or CHF (OR: 1.04, 95% CI: 0.98‐1.11). Medicaid insurance was associated with readmission for CHF (OR: 1.20, 95% CI: 1.12‐1.30) and PNA (OR: 1.28, 95% CI: 1.18‐1.38) but appeared to be protective from readmission for AMI (OR: 0.89, 95% CI: 0.83‐0.96). Lack of insurance was associated with decreased odds of readmission for all diagnoses (P<0.05 for all models).

Models predicting 90‐day readmission rates showed similar results in all categories; therefore, the data are not shown.

DISCUSSION

We used a California statewide discharge database that linked individual patient records from all nonfederal hospitals to examine 30‐ and 90‐day hospital readmissions for CHF, AMI, and PNA. We hypothesized, but did not find, that weekend hospital discharge would be associated with higher hospital readmission rates. We did find other factors that were associated with hospital readmissions, including race, age, greater comorbidities, male gender, and discharge to an SNF. Nearly half of patients were readmitted for the same diagnosis as the initial discharge diagnosis, and nearly two‐thirds of the patients were readmitted to a hospital different from the discharging hospital.

Our study found some findings similar to prior investigations. First, the factors that predicted hospital readmission were complex and included age, race, gender, comorbidities, payer status, length of hospital stay, and the occurrence of a complication; most of these factors persisted after multivariable analysis but were not necessarily consistent across all admission diagnoses.[16, 17, 18] One finding of particular interest was the impact of insurance status. Specifically, lack of insurance was inversely associated with hospital readmission; this finding warrants further investigation. Our study is also similar to others in that we found that the most common reasons for readmission are typically related to the reason for the principal admission. Dharmarajan et al. previously studied the reason for readmission among hospitalized Medicare patients with AMI, CHF, and PNA, and found similarly high rates of identical admission diagnoses.[19] Furthermore, in our study, between 32% and 65% of 30‐day readmissions were to a hospital different than the discharging facility. Although few prior studies have had the ability to assess readmission to alternative hospitals, those who have done so in the past have found similar rates of divergence from the index facility.[20, 21]

Despite the apparent similarities to other studies, the current research question was specifically designed to investigate the weekend effect of hospital discharge. The term weekend effect refers to a phenomenon of worse clinical outcomes (eg, morbidity,[22] mortality,[6, 7] intensive care unit [ICU] readmission,[23] delays in appropriate diagnostic imaging[24, 25] and intervention,[26, 27] LOS,[28] and hospital costs[29]) for care delivered on a weekend. In a landmark study, Bell and Redelmeier demonstrated increased in‐house mortality for patients with ruptured abdominal aortic aneurysm, pulmonary embolism, or acute epiglottitis admitted through the emergency department on a weekend compared to weekday.[6] After controlling for patient variables, the association persisted, suggesting system‐related factors were contributory. Similarly, Kostis et al. showed that patients admitted to the hospital on a weekend with AMI had higher 30‐day mortality rates compared to those with weekday admission.[7] Finally, Aylin et al. demonstrated that mortality was 44% higher for patients undergoing elective surgery on a Friday and 82% higher for surgery on a weekend compared to a Monday.[30]

Despite this robust literature, fewer studies have evaluated the relationship between timing of discharge and outcomes. Much of the initial research has been focused on timing of discharge from the ICU. For example, transfer out of the ICU at night has been associated with higher in‐hospital mortality[31, 32, 33, 34, 35] as well as ICU readmission.[36, 37] Discharge from the ICU on a weekend has been associated with increased mortality in some studies[23] but not in others.[35, 38] Van Walraven and Bell were the first to investigate the impact of weekend hospital discharge on outcomes. In their analysis of all discharges from Ontario hospitals between 1990 and 2000, patients discharged on a Friday were at increased risk of death and 30‐day readmission compared to discharge on a Wednesday.[9] Beck et al. performed a similar study in pediatric patients but did not find a statistically significant effect of Friday discharge on readmission rates.[39] McAlister et al. specifically studied the effect of weekend (Saturday or Sunday) discharge on patients with CHF by analyzing discharges from Alberta, Canada hospitals between 1999 and 2009. Despite being comprised of lower‐risk patients, weekend discharge was associated with greater rates of 30‐ and 90‐day death and hospital readmission.[10] Conversely, McAlister et al. evaluated general medicine discharges from teaching hospitals in Alberta, Canada between 2009 and 2011 and found no difference in hospital readmission rates among those discharged on a weekend versus weekday.[11] The current investigation is the first to study hospitals in the United States to address this topic, an important consideration given differences in American and Canadian healthcare systems. Nevertheless, our results are similar to those of McAlister et al.,[11] who found no difference in hospital readmission rates based on day of discharge among patients with AMI, CHF, or PNA.

One potential explanation for finding a lack of correlation between weekend discharge and readmissions is that patients at higher risk for readmission are already selected toward weekday discharge. Our study found that patients discharged to an SNF, a group with higher odds of readmission, were less often discharged on a weekend. There may be other unmeasurable factors that differ between patients discharged on weekends versus weekdays. Also, factors that bias healthcare providers' decision making on timing of discharge are difficult to quantify and may differ between the 2 groups. Although our study hypothesis was driven by the perception that weekend discharges may fare poorly because of inadequate resources on the weekend, an alternative explanation for finding no association may be that current systems in place already do an effective job of discharge coordination on the weekend. Despite fears that staffing and equipment are significantly reduced during the weekend, perhaps weekend discharge resources are not the limiting factor in efforts to reduce readmissions.

Our results challenge the idea that weekend discharges predict hospital readmissions in California and argue for the relative safety of weekend discharges. Based on these findings, the routine delay in discharge of the complex medical patient until Monday for fear of discharge on a weekend does not seem warranted. Avoiding unnecessary delays in discharge should have positive effects on healthcare costs by reducing LOS. Two additional implications of our work are that single institution studies may underestimate readmission rates,[40] and that discharge to an SNF should receive special consideration in calculation of hospital‐level penalties for subsequent readmissions, as this group is associated with particularly higher risk.

There are some limitations to our study that should be acknowledged. The use of administrative data has well known limitations and the possibility of coding inaccuracy cannot be excluded.[41] Certain factors that could potentially differ between groups, such as illness severity, as well as details on the discharge process, were not available in this administrative database. In addition, elective readmissions were not excluded from the study. Also, because of the way the data were coded, a significant percentage of discharge dispositions were unknown. Finally, although morbidity and mortality have been studied in previous reports,[9, 10, 39] these data were not available for the current study, limiting the applicability of its conclusions.

CONCLUSIONS

In conclusion, among patients admitted with AMI, CHF, or PNA in California, discharge on a weekend is not associated with hospital readmission. Future studies on hospital readmissions should use a population‐based approach to accurately capture all readmissions following discharge.

Acknowledgments

Disclosure: Nothing to report.

References
  1. Benbassat J, Taragin M. Hospital readmissions as a measure of quality of health care: advantages and limitations. Arch Intern Med. 2000;160(8):10741081.
  2. Kocher RP, Adashi EY. Hospital readmissions and the Affordable Care Act: paying for coordinated quality care. JAMA. 2011;306(16):17941795.
  3. Rau J. Medicare fines 2,610 hospitals in third round of readmission penalties. Kaiser Health News. Available at: http://www.kaiserhealthnews.org/Stories/2014/October/02/Medicare‐readmissions‐penalties‐2015.aspx. Published October 2, 2014. Accessed October 2, 2014.
  4. Burke RE, Coleman EA. Interventions to decrease hospital readmissions: keys for cost‐effectiveness. JAMA Intern Med. 2013;173(8):695698.
  5. Hansen LO, Young RS, Hinami K, Leung A, Williams MV. Interventions to reduce 30‐day rehospitalization: a systematic review. Ann Intern Med. 2011;155(8):520528.
  6. Bell CM, Redelmeier DA. Mortality among patients admitted to hospitals on weekends as compared with weekdays. N Engl J Med. 2001;345(9):663668.
  7. Kostis WJ, Demissie K, Marcella SW, et al. Weekend versus weekday admission and mortality from myocardial infarction. N Engl J Med. 2007;356(11):10991109.
  8. Ricciardi R, Roberts PL, Read TE, Baxter NN, Marcello PW, Schoetz DJ. Mortality rate after nonelective hospital admission. Arch Surg 2011;146(5):545551.
  9. Walraven C, Bell CM. Risk of death or readmission among people discharged from hospital on Fridays. CMAJ. 2002;166(13):16721673.
  10. McAlister FA, Au AG, Majumdar SR, Youngson E, Padwal RS. Postdischarge outcomes in heart failure are better for teaching hospitals and weekday discharges. Circ Heart Fail. 2013;6(5):922929.
  11. McAlister FA, Youngson E, Padwal RS, Majumdar SR. Similar outcomes among general medicine patients discharged on weekends. J Hosp Med. 2015;10(2):6974.
  12. Misky GJ, Wald HL, Coleman EA. Post‐hospitalization transitions: examining the effects of timing of primary care provider follow‐up. J Hosp Med. 2010;5(7):392397.
  13. Forster AJ, Murff HJ, Peterson JF, Gandhi TK, Bates DW. The incidence and severity of adverse events affecting patients after discharge from the hospital. Ann Intern Med. 2003;138(3):161167.
  14. Cornish PL, Knowles SR, Marchesano R, et al. Unintended medication discrepancies at the time of hospital admission. Arch Intern Med. 2005;165(4):424429.
  15. Readmissions Reduction Program. August 2014. Available at: http://www.cms.gov/Medicare/Medicare‐Fee‐for‐Service‐Payment/AcuteInpatientPPS/Readmissions‐Reduction‐Program.html. Accessed October 2, 2014.
  16. Joynt KE, Orav EJ, Jha AK. Thirty‐day readmission rates for Medicare beneficiaries by race and site of care. JAMA. 2011;305(7):675681.
  17. Hasan O, Meltzer DO, Shaykevich SA, et al. Hospital readmission in general medicine patients: a prediction model. J Gen Intern Med. 2009;25(3):211219.
  18. Jencks SF, Williams MV, Coleman EA. Rehospitalizations among patients in the Medicare fee‐for‐service program. N Engl J Med. 2009;360(14):14181428.
  19. Dharmarajan K, Hsieh AF, Lin Z, et al. Diagnoses and timing of 30‐day readmissions after hospitalization for heart failure, acute myocardial infarction, or pneumonia. JAMA. 2013;309(4):355363.
  20. Yermilov I, Bentrem D, Sekeris E, et al. Readmissions following pancreaticoduodenectomy for pancreas cancer: a population‐based appraisal. Ann Surg Oncol. 2009;16(3):554561.
  21. Nasir K, Lin Z, Bueno H, et al. Is same‐hospital readmission rate a good surrogate for all‐hospital readmission rate? Med Care. 2010;48(5):477481.
  22. Worni M, Schudel IM, Østbye T, et al. Worse outcomes in patients undergoing urgent surgery for left‐sided diverticulitis admitted on weekends vs weekdays: a population‐based study of 31 832 patients. Arch Surg. 2012;147(7):649655.
  23. Obel N, Schierbeck J, Pedersen L, et al. Mortality after discharge from the intensive care unit during the early weekend period: a population‐based cohort study in Denmark. Acta Anaesthesiol Scand. 2007;51(9):12251230.
  24. Sheppard JP, Mant J, Quinn T, McManus RJ. Something for the weekend? JAMA Neurol. 2013;70(1):130.
  25. Palmer WL, Bottle A, Davie C, Vincent CA, Aylin P. Dying for the weekend: a retrospective cohort study on the association between day of hospital presentation and the quality and safety of stroke care. Arch Neurol. 2012;69(10):12961302.
  26. Groves EM, Khoshchehreh M, Le C, Malik S. Effects of weekend admission on the outcomes and management of ruptured aortic aneurysms. J Vasc Surg. 2014;60(2):318324
  27. Parikh SV, Jacobi JA, Chu E, et al. Treatment delay in patients undergoing primary percutaneous coronary intervention for ST‐elevation myocardial infarction: a key process analysis of patient and program factors. Am Heart J. 2008;155(2):290297.
  28. Horwich TB, Hernandez AF, Liang L, et al. Weekend hospital admission and discharge for heart failure: association with quality of care and clinical outcomes. Am Heart J. 2009;158(3):451458.
  29. Nandyala SV, Marquez‐Lara A, Fineberg SJ, Schmitt DR, Singh K. Comparison of perioperative outcomes and cost of spinal fusion for cervical trauma: weekday versus weekend admissions. Spine. 2013;38(25):21782183.
  30. Aylin P, Alexandrescu R, Jen MH, Mayer EK, Bottle A. Day of week of procedure and 30 day mortality for elective surgery: retrospective analysis of hospital episode statistics. BMJ. 2013;346:f2424.
  31. Goldfrad C, Rowan K. Consequences of discharges from intensive care at night. Lancet. 2000;355(9210):11381142.
  32. Beck DH, McQuillan P, Smith GB. Waiting for the break of dawn? The effects of discharge time, discharge TISS scores and discharge facility on hospital mortality after intensive care. Intensive Care Med. 2002;28(9):12871293.
  33. Tobin AE, Santamaria JD. After‐hours discharges from intensive care are associated with increased mortality. Med J Aust. 2006;184(7):334337.
  34. Priestap FA, Martin CM. Impact of intensive care unit discharge time on patient outcome. Crit Care Med. 2006;34(12):29462951.
  35. Laupland KB, Shahpori R, Kirkpatrick AW, Stelfox HT. Hospital mortality among adults admitted to and discharged from intensive care on weekends and evenings. J Crit Care. 2008;23(3):317324.
  36. Renton J, Pilcher DV, Santamaria JD, et al. Factors associated with increased risk of readmission to intensive care in Australia. Intensive Care Med. 2011;37(11):18001808.
  37. Pilcher DV, Duke GJ, George C, Bailey MJ, Hart G. After‐hours discharge from intensive care increases the risk of readmission and death. Anaesth Intensive Care. 2007;35(4):477485.
  38. Uusaro A, Kari A, Ruokonen E. The effects of ICU admission and discharge times on mortality in Finland. Intensive Care Med. 2003;29(12):21442148.
  39. Beck CE, Khambalia A, Parkin PC, Raina P, Macarthur C. Day of discharge and hospital readmission rates within 30 days in children: a population‐based study. Paediatr Child Health. 2006;11(7):409412.
  40. Gonzalez AA, Shih T, Dimick JB, Ghaferi AA. Using same‐hospital readmission rates to estimate all‐hospital readmission rates. J Am Coll Surg. 2014;219(4):656663.
  41. Sacks GD, Dawes AJ, Russell MM, et al. Evaluation of hospital readmissions in surgical patients: do administrative data tell the real story? JAMA Surg. 2014;149(8):759764.
References
  1. Benbassat J, Taragin M. Hospital readmissions as a measure of quality of health care: advantages and limitations. Arch Intern Med. 2000;160(8):10741081.
  2. Kocher RP, Adashi EY. Hospital readmissions and the Affordable Care Act: paying for coordinated quality care. JAMA. 2011;306(16):17941795.
  3. Rau J. Medicare fines 2,610 hospitals in third round of readmission penalties. Kaiser Health News. Available at: http://www.kaiserhealthnews.org/Stories/2014/October/02/Medicare‐readmissions‐penalties‐2015.aspx. Published October 2, 2014. Accessed October 2, 2014.
  4. Burke RE, Coleman EA. Interventions to decrease hospital readmissions: keys for cost‐effectiveness. JAMA Intern Med. 2013;173(8):695698.
  5. Hansen LO, Young RS, Hinami K, Leung A, Williams MV. Interventions to reduce 30‐day rehospitalization: a systematic review. Ann Intern Med. 2011;155(8):520528.
  6. Bell CM, Redelmeier DA. Mortality among patients admitted to hospitals on weekends as compared with weekdays. N Engl J Med. 2001;345(9):663668.
  7. Kostis WJ, Demissie K, Marcella SW, et al. Weekend versus weekday admission and mortality from myocardial infarction. N Engl J Med. 2007;356(11):10991109.
  8. Ricciardi R, Roberts PL, Read TE, Baxter NN, Marcello PW, Schoetz DJ. Mortality rate after nonelective hospital admission. Arch Surg 2011;146(5):545551.
  9. Walraven C, Bell CM. Risk of death or readmission among people discharged from hospital on Fridays. CMAJ. 2002;166(13):16721673.
  10. McAlister FA, Au AG, Majumdar SR, Youngson E, Padwal RS. Postdischarge outcomes in heart failure are better for teaching hospitals and weekday discharges. Circ Heart Fail. 2013;6(5):922929.
  11. McAlister FA, Youngson E, Padwal RS, Majumdar SR. Similar outcomes among general medicine patients discharged on weekends. J Hosp Med. 2015;10(2):6974.
  12. Misky GJ, Wald HL, Coleman EA. Post‐hospitalization transitions: examining the effects of timing of primary care provider follow‐up. J Hosp Med. 2010;5(7):392397.
  13. Forster AJ, Murff HJ, Peterson JF, Gandhi TK, Bates DW. The incidence and severity of adverse events affecting patients after discharge from the hospital. Ann Intern Med. 2003;138(3):161167.
  14. Cornish PL, Knowles SR, Marchesano R, et al. Unintended medication discrepancies at the time of hospital admission. Arch Intern Med. 2005;165(4):424429.
  15. Readmissions Reduction Program. August 2014. Available at: http://www.cms.gov/Medicare/Medicare‐Fee‐for‐Service‐Payment/AcuteInpatientPPS/Readmissions‐Reduction‐Program.html. Accessed October 2, 2014.
  16. Joynt KE, Orav EJ, Jha AK. Thirty‐day readmission rates for Medicare beneficiaries by race and site of care. JAMA. 2011;305(7):675681.
  17. Hasan O, Meltzer DO, Shaykevich SA, et al. Hospital readmission in general medicine patients: a prediction model. J Gen Intern Med. 2009;25(3):211219.
  18. Jencks SF, Williams MV, Coleman EA. Rehospitalizations among patients in the Medicare fee‐for‐service program. N Engl J Med. 2009;360(14):14181428.
  19. Dharmarajan K, Hsieh AF, Lin Z, et al. Diagnoses and timing of 30‐day readmissions after hospitalization for heart failure, acute myocardial infarction, or pneumonia. JAMA. 2013;309(4):355363.
  20. Yermilov I, Bentrem D, Sekeris E, et al. Readmissions following pancreaticoduodenectomy for pancreas cancer: a population‐based appraisal. Ann Surg Oncol. 2009;16(3):554561.
  21. Nasir K, Lin Z, Bueno H, et al. Is same‐hospital readmission rate a good surrogate for all‐hospital readmission rate? Med Care. 2010;48(5):477481.
  22. Worni M, Schudel IM, Østbye T, et al. Worse outcomes in patients undergoing urgent surgery for left‐sided diverticulitis admitted on weekends vs weekdays: a population‐based study of 31 832 patients. Arch Surg. 2012;147(7):649655.
  23. Obel N, Schierbeck J, Pedersen L, et al. Mortality after discharge from the intensive care unit during the early weekend period: a population‐based cohort study in Denmark. Acta Anaesthesiol Scand. 2007;51(9):12251230.
  24. Sheppard JP, Mant J, Quinn T, McManus RJ. Something for the weekend? JAMA Neurol. 2013;70(1):130.
  25. Palmer WL, Bottle A, Davie C, Vincent CA, Aylin P. Dying for the weekend: a retrospective cohort study on the association between day of hospital presentation and the quality and safety of stroke care. Arch Neurol. 2012;69(10):12961302.
  26. Groves EM, Khoshchehreh M, Le C, Malik S. Effects of weekend admission on the outcomes and management of ruptured aortic aneurysms. J Vasc Surg. 2014;60(2):318324
  27. Parikh SV, Jacobi JA, Chu E, et al. Treatment delay in patients undergoing primary percutaneous coronary intervention for ST‐elevation myocardial infarction: a key process analysis of patient and program factors. Am Heart J. 2008;155(2):290297.
  28. Horwich TB, Hernandez AF, Liang L, et al. Weekend hospital admission and discharge for heart failure: association with quality of care and clinical outcomes. Am Heart J. 2009;158(3):451458.
  29. Nandyala SV, Marquez‐Lara A, Fineberg SJ, Schmitt DR, Singh K. Comparison of perioperative outcomes and cost of spinal fusion for cervical trauma: weekday versus weekend admissions. Spine. 2013;38(25):21782183.
  30. Aylin P, Alexandrescu R, Jen MH, Mayer EK, Bottle A. Day of week of procedure and 30 day mortality for elective surgery: retrospective analysis of hospital episode statistics. BMJ. 2013;346:f2424.
  31. Goldfrad C, Rowan K. Consequences of discharges from intensive care at night. Lancet. 2000;355(9210):11381142.
  32. Beck DH, McQuillan P, Smith GB. Waiting for the break of dawn? The effects of discharge time, discharge TISS scores and discharge facility on hospital mortality after intensive care. Intensive Care Med. 2002;28(9):12871293.
  33. Tobin AE, Santamaria JD. After‐hours discharges from intensive care are associated with increased mortality. Med J Aust. 2006;184(7):334337.
  34. Priestap FA, Martin CM. Impact of intensive care unit discharge time on patient outcome. Crit Care Med. 2006;34(12):29462951.
  35. Laupland KB, Shahpori R, Kirkpatrick AW, Stelfox HT. Hospital mortality among adults admitted to and discharged from intensive care on weekends and evenings. J Crit Care. 2008;23(3):317324.
  36. Renton J, Pilcher DV, Santamaria JD, et al. Factors associated with increased risk of readmission to intensive care in Australia. Intensive Care Med. 2011;37(11):18001808.
  37. Pilcher DV, Duke GJ, George C, Bailey MJ, Hart G. After‐hours discharge from intensive care increases the risk of readmission and death. Anaesth Intensive Care. 2007;35(4):477485.
  38. Uusaro A, Kari A, Ruokonen E. The effects of ICU admission and discharge times on mortality in Finland. Intensive Care Med. 2003;29(12):21442148.
  39. Beck CE, Khambalia A, Parkin PC, Raina P, Macarthur C. Day of discharge and hospital readmission rates within 30 days in children: a population‐based study. Paediatr Child Health. 2006;11(7):409412.
  40. Gonzalez AA, Shih T, Dimick JB, Ghaferi AA. Using same‐hospital readmission rates to estimate all‐hospital readmission rates. J Am Coll Surg. 2014;219(4):656663.
  41. Sacks GD, Dawes AJ, Russell MM, et al. Evaluation of hospital readmissions in surgical patients: do administrative data tell the real story? JAMA Surg. 2014;149(8):759764.
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Address for correspondence and reprint requests: Jordan Cloyd, MD, Department of Surgery, Stanford University, 300 Pasteur Dr., MC5641, Stanford, CA 94305; Telephone: 650‐464‐8915; Fax: 650‐852‐3430; E‐mail: [email protected]
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David Henry's JCSO podcast, June 2015

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This month, Dr David Henry of The Journal of Community and Supportive Oncology examines the use olaparib, which was recently approved for the treatment of BRCA-mutated advanced ovarian cancer, as well as four Original Research articles that focus on patient care, support, and quality of life. There’s a comparison of the antiemetic efficacy and safety of palonosetron and ondansetron in the prevention of chemotherapy-induced nausea and vomiting in children; a study that looks at the rationale, dosimetric parameters, and preliminary clinical outcomes in patients who undergo postoperative stereotactic radiosurgery with simultaneous integrated boost for brain metastases; an examination of the impact of nurse navigation on the timeliness of diagnostic medical services in patients with newly diagnosed lung cancer; and a study that draws on a novel approach to improving end-of-life care by measuring patterns of care among recently deceased patients. The podcast concludes with a round-up of some recent studies on cardiovascular disease in oncology, including the toxicity of cancer therapy and treatment guidelines from the American Society of Clinical Oncology.

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This month, Dr David Henry of The Journal of Community and Supportive Oncology examines the use olaparib, which was recently approved for the treatment of BRCA-mutated advanced ovarian cancer, as well as four Original Research articles that focus on patient care, support, and quality of life. There’s a comparison of the antiemetic efficacy and safety of palonosetron and ondansetron in the prevention of chemotherapy-induced nausea and vomiting in children; a study that looks at the rationale, dosimetric parameters, and preliminary clinical outcomes in patients who undergo postoperative stereotactic radiosurgery with simultaneous integrated boost for brain metastases; an examination of the impact of nurse navigation on the timeliness of diagnostic medical services in patients with newly diagnosed lung cancer; and a study that draws on a novel approach to improving end-of-life care by measuring patterns of care among recently deceased patients. The podcast concludes with a round-up of some recent studies on cardiovascular disease in oncology, including the toxicity of cancer therapy and treatment guidelines from the American Society of Clinical Oncology.

This month, Dr David Henry of The Journal of Community and Supportive Oncology examines the use olaparib, which was recently approved for the treatment of BRCA-mutated advanced ovarian cancer, as well as four Original Research articles that focus on patient care, support, and quality of life. There’s a comparison of the antiemetic efficacy and safety of palonosetron and ondansetron in the prevention of chemotherapy-induced nausea and vomiting in children; a study that looks at the rationale, dosimetric parameters, and preliminary clinical outcomes in patients who undergo postoperative stereotactic radiosurgery with simultaneous integrated boost for brain metastases; an examination of the impact of nurse navigation on the timeliness of diagnostic medical services in patients with newly diagnosed lung cancer; and a study that draws on a novel approach to improving end-of-life care by measuring patterns of care among recently deceased patients. The podcast concludes with a round-up of some recent studies on cardiovascular disease in oncology, including the toxicity of cancer therapy and treatment guidelines from the American Society of Clinical Oncology.

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VIDEO: Anticipatory guidance can reduce chronic postconcussion syndrome

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WASHINGTON – Regardless of the number of tests and tools for helping to diagnose pediatric sports concussions, Dr. Christopher Giza, professor of pediatric neurology and neurosurgery at the University of California, Los Angeles, says it’s important for clinicians to remember that “concussion is a clinical diagnosis.”

In this video interview recorded at Summit in Neurology & Psychiatry, Dr. Giza offers pearls and insights into the latest in sports concussion management. He describes the four “Rs” of treating sports concussions and urges primary care personnel to offer anticipatory guidance to patients and their families. Such guidance can lead to a 20% decrease in chronic postconcussion syndrome in children and adolescents, he said at the meeting held by Global Academy for Medical Education. Global Academy and this news organization are owned by the same company.

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WASHINGTON – Regardless of the number of tests and tools for helping to diagnose pediatric sports concussions, Dr. Christopher Giza, professor of pediatric neurology and neurosurgery at the University of California, Los Angeles, says it’s important for clinicians to remember that “concussion is a clinical diagnosis.”

In this video interview recorded at Summit in Neurology & Psychiatry, Dr. Giza offers pearls and insights into the latest in sports concussion management. He describes the four “Rs” of treating sports concussions and urges primary care personnel to offer anticipatory guidance to patients and their families. Such guidance can lead to a 20% decrease in chronic postconcussion syndrome in children and adolescents, he said at the meeting held by Global Academy for Medical Education. Global Academy and this news organization are owned by the same company.

The video associated with this article is no longer available on this site. Please view all of our videos on the MDedge YouTube channel

[email protected]

On Twitter @whitneymcknight

WASHINGTON – Regardless of the number of tests and tools for helping to diagnose pediatric sports concussions, Dr. Christopher Giza, professor of pediatric neurology and neurosurgery at the University of California, Los Angeles, says it’s important for clinicians to remember that “concussion is a clinical diagnosis.”

In this video interview recorded at Summit in Neurology & Psychiatry, Dr. Giza offers pearls and insights into the latest in sports concussion management. He describes the four “Rs” of treating sports concussions and urges primary care personnel to offer anticipatory guidance to patients and their families. Such guidance can lead to a 20% decrease in chronic postconcussion syndrome in children and adolescents, he said at the meeting held by Global Academy for Medical Education. Global Academy and this news organization are owned by the same company.

The video associated with this article is no longer available on this site. Please view all of our videos on the MDedge YouTube channel

[email protected]

On Twitter @whitneymcknight

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VIDEO: Anticipatory guidance can reduce chronic postconcussion syndrome
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AT SUMMIT IN NEUROLOGY & PSYCHIATRY

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