Objective In the 30 days after hospital discharge, hospital utilisation is common and costly. This study evaluated the association between gender and hospital utilisation within 30 days of discharge.
Design Secondary data analysis using Poisson regression stratified by gender.
Participants 737 English-speaking hospitalised adults from general medical service in urban, academic safety-net medical centre who participated in the Project Re-Engineered clinical trial (clinicaltrials.gov identifier: NCT00252057).
Main outcome measure The primary end point was hospital utilisation, defined as total emergency department visits and hospital readmissions within 30 days after index discharge.
Results Female subjects had a rate of 29 events for every 100 people and male subjects had a rate of 47 events for every 100 people (incident rate ratio (IRR) 1.62, 95% CI 1.28 to 2.06). Among men, risk factors included hospital utilisation in the 6 months prior to the index hospitalisation (IRR 3.55, 95% CI 2.38 to 5.29), being unmarried (IRR 1.72, 95% CI 1.12 to 2.64), having a positive depression screen (IRR 1.53, 95% CI 1.09 to 2.13) and no primary care physician (PCP) visit within 30 days (IRR 1.64, 95% CI 1.08 to 2.50). Among women, the only risk factor was hospital utilisation in the 6 months prior to the index hospitalisation (IRR 3.08, 95% CI 1.86 to 5.10).
Conclusions In our data, male subjects had a higher rate of hospital utilisation within 30 days of discharge than female subjects. For men—but not for women—risk factors were being retired, unmarried, having depressive symptoms and having no PCP visit within 30 days. Interventions addressing these factors might lower hospital utilisation rates observed among men.
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Early hospital readmission is a common and costly occurrence in the USA. Men often use hospital emergency departments for usual source of medical care.
We aimed to study whether men are therefore more likely to be readmitted to the hospital within 30 days of an index discharge.
Men have higher rates of 30-day readmission to hospital than women in this study group. Men also were less likely to complete a follow-up appointment with their primary care physician after discharge.
Interventions that promote connecting men to primary care, address social isolation and screen for depressive symptoms may reduce the risk for early readmission among men.
Strengths and limitations of this study
This analysis was conducted with the Project RED data set, which included, and allowed controlling for certain clinical and social confounders in our analysis such as subjects' comorbidity burden, depression symptoms, homelessness, substance abuse and other similar risk factors, in our analysis.
This study is limited in that it was conducted at an urban safety-net hospital and may not be generalisable to other types of hospital systems.
We also relied on subject self-report of any rehospitalisation events outside of the study site, however, were able to confirm 91% of all events using our hospital electronic medical record system.
Hospital utilisation in the 30 days after discharge is costly and may be a marker of poor quality of care. In 2004, the cost for hospital readmissions among Medicare recipients was estimated to be US $17.4 billion.1 Accordingly, the Affordable Care Act includes multiple provisions designed to improve care transitions. The act includes both funding to stimulate hospitals and community-based providers to coordinate post-discharge services and a programme to withhold payments, of progressively increasing amounts, to hospitals that demonstrate higher rates of readmission within 30 days after discharge.2 The extent to which readmissions are preventable is debated.3 4 However, given the magnitude of the problem, even a moderate reduction in unnecessary readmissions could have a large economic impact. In fact, we have shown that hospital readmissions can be moderately reduced.5
With prospective identification of patients at high risk of being readmitted, providers could potentially direct resources to prevent the readmission. In order to fulfil this goal in an efficient and effective manner, providers will need to be able to identify the patients with high risk and may need to understand how to adapt services according to the risk factors identified.
Several factor associated with 30-day rehospitalisation have been well characterised. These include older age,6 7 comorbidity,7 income level,8 history of prior hospitalisation,6 7 increased length of stay in the index hospitalisation,9 minority ethnicity,7 10 depressive symptoms,11 12 alcohol and drug use10 and specific clinical conditions (eg, congestive heart failure).6 7 The role of male gender as a risk factor for post-discharge hospital utilisation has been noted in several disease-specific contexts; yet, to our knowledge, no study of post-discharge hospital utilisation has focused on gender. While gender is not typically considered a modifiable factor, established patterns of health service utilisation that are associated with gender (ie, lower rates of preventive care and fewer visits to primary care among men) may put men at higher risk for poor outcomes after hospital discharge.13
Therefore, we conducted a secondary analysis of the Re-engineered Discharge (RED) clinical trial data set to assess the association between gender and the rate of post-discharge hospital utilisation among a cohort of adult patients hospitalised in an urban safety-net hospital. In addition, we sought to identify potential factors contributing to gender-based differences.
A full description of the methods for the Project RED trial has been described previously.5 Briefly, the Project RED trial was a two-armed randomised controlled trial of English-speaking adult patients, 18 years or older, admitted to the teaching service of Boston Medical Center. Seven hundred and forty-nine subjects were enrolled and randomised: 376 in the usual care arm and 373 in the intervention arm. Patients had to have a telephone, be able to comprehend study details and the consent process in English and have plans to be discharged to a US community. Patients were not enrolled if they were admitted from a skilled nursing facility or other hospital, transferred to a different hospital service, admitted for a planned hospitalisation, on hospital precautions, on suicide watch, deaf or blind. A total of 3873 were assessed for eligibility. Due to a lack of available research staff, 1616 patients were not assessed. Of those assessed for eligibility, 1049 did not meet eligibility criteria, 120 were previously enrolled, 527 refused to participate, 474 were unavailable in their hospital room at the time of enrolment and 954 were not approached because the maximum enrolled subject number was reached that day. Seven hundred and forty-nine subjects were enrolled and randomised: 376 in the usual care arm and 373 in the intervention arm. The Institutional Review Board of Boston University approved all study activities. Baseline demographic and clinical characteristics were similar across the study arms.
The primary outcome was the rate of post-discharge hospital utilisation, defined as the total number of emergency department (ED) visits and readmissions per subject, within 30 days of their index discharge. Any ED visit in which a subject was subsequently admitted to the hospital was only counted as a readmission.
Primary independent variable and covariates
The primary independent variable, gender (male or female), was defined by the hospital electronic medical record (EMR). Potential confounders were identified a priori from the literature on factors associated with post-discharge hospital utilisation and gender including age, marital status, health literacy score,14 Charlson score,15 insurance type, employment status, income level, homeless status, hospital utilisation within the 6 months prior to the index hospitalisation, educational attainment, length of hospital stay, race/ethnicity, depressive symptoms and Project RED study group assignment.
Outcome data were collected by Project RED research staff, blinded to group assignment, by review of the hospital's EMRs and by contacting subjects by telephone 30 days post-discharge. Dates of subsequent ED visits and readmissions at Boston Medical Center were obtained from the EMRs, while those at other hospitals were collected through subject report. Those subjects who could not be reached within 60 days post-discharge were assumed alive and hospital EMRs were relied upon for primary outcomes. Randomisation provided a balanced study sample, with an equal proportion of male and female participants assigned to each arm of the original trial. Of 749 subjects who had participated in a randomised clinical trial (Project RED), 737 participants were included in this secondary analysis and 12 subjects were removed due to death prior to index discharge,6 requested removal,13 previously enrolled1 and missing data.1 Data for selected covariates were collected by self-report (age, race, income, marital status, education attainment, employment status, insurance type, homelessness) or using validated tools (health literacy, depressive symptoms) or EMR (length of stay, prior utilisation, Charlson score).
Socio-demographic and clinical characteristics of the subjects were compared by gender. Bivariate analyses were conducted to identify gender differences and potential confounders between gender and post-discharge hospital utilisation within 30 days of index discharge. χ2 Tests were utilised for categorical variables and t tests for continuous variables. A Poisson regression was conducted using relevant potential confounders to construct the final best-fit model determining the strength of association between gender and hospital utilisation. Several interaction terms in our initial Poisson regression were significant. We therefore decided to evaluate potential interactions between gender and hospital utilisation using a stratified Poisson regression analysis.
Age, length of stay and Charlson score were used as continuous variables. Gender (male or female), marital status (married, not married) and homelessness (homeless within the last 3 months) were treated as dichotomous variables. Categorical variables were created for prior hospital utilisation (no prior visits, one to two prior visits or three or more prior visits in the previous 6 months), educational attainment (less than high school graduate, high school graduate or GED or any college), insurance type (Medicare, Medicaid, private insurance or Massachusetts State Subsidised Free Care), income level (no income, <$10 000/year, $10 000–20 000, $20 000 or more or declined to answer), level of health literacy (grade 3 and below, grades 4–6, grades 7–8 or grade 9 and above) according to the Rapid Estimate of Adult Literacy in Medicine and employment status (employed, not employed, disabled, retired or other).
Hospital utilisation is defined as the sum of emergency room visits and hospitalisations (an emergency room visit that leads to a hospitalisation is counted only as a hospitalisation). Hospital utilisation incidence rates were calculated as the number of hospital utilisation events within 30 days of discharge per subject. Person-time was measured in months. The unadjusted incident rate ratio (IRR) was calculated as the ratio of the rate of hospital utilisation among male patients versus female patients using Poisson regression. p Values and CIs were corrected for over dispersion if necessary.
Poisson models were used to test for statistically significant differences in the number of post-discharge hospital utilisation events at 30 days. Two-sided significance tests were used. p Values of <0.05 were considered to indicate statistical significance. A Kaplan–Meier survival curve was generated for the time to multiple hospital utilisation events for the 30-day period following the index discharge and compared using a log-rank test. All data were analysed with S-Plus 8.0.
The analytic cohort included 367 male subjects and 370 female subjects. Socio-demographic, healthcare utilisation and health status indicator variables, stratified by gender, are shown in table 1. Gender differences existed among a number of variables. For example, male subjects were approximately 4 years younger and were more likely to be white non-Hispanic or Hispanic and less likely black non-Hispanic than female subjects. Men reported a relatively higher income, with almost 10% more men reporting an annual personal income of $20 000 or more compared with women. Male subjects were more likely to have private insurance, while female subjects were more likely to have Medicaid. Women reported having a primary care physician (PCP) at baseline at a significantly higher rate than men (88% vs 74%, p<0.001). Women also had higher levels of depressive symptoms (Patient Health Questionnaire-9, 2.5 vs 1.9), were more likely to report a history of having been diagnosed as having depression (46% vs 26%) and were more likely to report currently taking medicine for depression (26% vs 13%).
Female subjects had a rate of 29 events per 100 people per month and male subjects had a rate of 47 events per 100 people per month (IRR 1.62, 95% CI 1.28 to 2.06) (table 2). This difference is largely attributable to a higher rate of ED visits among male subjects (IRR 2.04, 95% CI 1.45 to 2.86). Furthermore, Kaplan–Meier survival curves for the time to multiple hospital utilisation events in the 30 days following index discharge showed that men were more likely to return to the hospital (p=0.04) (figure 1). At the 30-day follow-up telephone call, fewer men reported understanding their appointments after leaving the hospital compared with women (78% and 87%, p=0.005, respectively) (table 2). In addition, at 30 days post-discharge, women reported visiting their PCPs at a higher rate within the 30 days after their hospital discharge (57% and 49%, p=0.04, respectively).
Risk factors for hospital reutilisation by gender
A Poisson regression that is stratified by gender is shown in table 3. The model is controlled for age, previous hospital visits, employment, marital status, depression, study group, having a PCP at baseline and attending a PCP appointment. Among women, the only predictive factor was hospital utilisation in the 6 months prior to the index hospitalisation. Prior hospitalisation was also a risk factor for returning to the hospital within 30 days among men; however, additional significant factors were (1) being retired, (2) not married, (3) having a positive depression screen, (4) reporting no PCP visit within 30 days and (5) not being reached for the follow-up call at 30 days.
Among our subjects, we found that men have a higher rate of hospital utilisation within 30 days of hospital discharge than women. ED visits accounted for most of this difference. Among both men and women, prior hospital utilisation is predictive of future utilisation; however, risk factors including being retired, unmarried and having a positive depression screen were identified as risk factors exclusively in men. Additionally, men fared more poorly at understanding and attending their follow-up appointments, which also appeared to be an independent risk factor for returning to the hospital for men in this study.
Identifying and addressing risk factors associated with early post-discharge hospital utilisation is useful so that resources can be efficiently tailored to each individual patient's risk profile. Ideally, methods to ameliorate important risk factors are available. Some risk factors, like gender, however, may seem inherently immutable. Yet, as we demonstrated in this study, male gender is associated with other parameters that could potentially be effectively targeted.
Our findings raise the possibility that social isolation—as illustrated by the positive association with being retired, unmarried and symptoms of depression—may be important factors to target for intervention. Supporting these findings are studies examining the impact of social support and social networks. These studies have found that, in general, men are more socially isolated than women and that this contributes to worse health outcomes among men.13 16 Men who were socially isolated were found to be less likely to undergo screening for blood pressure, cholesterol and cancer.16
Other studies suggest that men report less help-seeking behaviours, use primary care less10 and are less likely to have a primary care physician when compared with women.13 Overall, women use more health services than men due to pregnancy and cervical and breast cancer screening programmes.6 However, lower rate of connectedness to primary care among men may also contribute to their excess use of hospital services and the finding that they may delay accessing care when it is needed.17 Perhaps paradoxically, one study showed that increased access to primary care actually increased subsequent hospital utilisation; however, this study was conducted in the VA with almost exclusively male subjects and may have reflected appropriate use of hospital services among those who had been previously underserved.18 Evidence suggests other factors that may impact a man's health-seeking behaviour including (1) men may have an overly optimistic perception of their health status, (2) the role women play in care-seeking decisions of men, (3) the influence of social networks and mood disorders and (4) the relatively lower value men appear to place on preventive care.13 17
Mood disorders can exacerbate the impact of social isolation on health. Men are far less likely than women to seek help for depression or anxiety.19 Even when they do present for care, depression is often misdiagnosed or overlooked by providers.20 These differences may be due to the differences in perceptions of distress experienced by men and women but may contribute to the low help-seeking behaviours exhibited by men. Still, given the effective treatment available for depression and anxiety disorders, depression represents a targetable risk for reducing unwarranted hospital utilisation by men.
This analysis suggests that approaches to mitigate the risk of post-discharge rehospitalisations or ED visits among men may be to develop interventions that promote a connection to primary care, address social isolation and diagnose and treat depressive symptoms. Addressing these risks will require a creative and innovative approach including methods like routine screening for depressive symptoms, more aggressive empowerment of patients to engage the healthcare system proactively rather than reactively and establishing group visits within primary care to foster a social environment paired with the provision of primary care services and health education, as has been used in diabetes care and other chronic illnesses.21
This study has several limitations. Data on hospital utilisation outside Boston Medical Center were determined using patient self-report and not confirmed by EMR review at other hospitals. We were, however, able to confirm 91% of all events by consulting our own EMR. Second, our results may not be generalisable to populations other than those served by urban safety-net hospitals or other populations excluded from the RED trial (eg, non-English-speaking patients and patients admitted from nursing homes). Third, not all patients were reached at 30 days for the follow-up phone call, which is how the information regarding PCP follow-up was gathered. Finally, having done our project in Massachusetts, our population may have had an uncommonly high level of access to primary care.
In summary, our findings suggest that male gender is an important risk factor for early unplanned hospital utilisation within 30 days of discharge. This association may be linked to social behavioural patterns commonly associated with male gender, such as delayed help-seeking behaviours, often resulting in sporadic and episodic use of health services by men. Interventions targeting factors at the root of this phenomenon—such as social isolation, low rates of primary and preventive healthcare use and treatment of depressive symptoms—may help mitigate this gender effect. As health insurance reform and workforce development in primary care evolve, special efforts may be needed to acculturate men to the use of outpatient services.
This web only file has been produced by the BMJ Publishing Group from an electronic file supplied by the author(s) and has not been edited for content.
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SM is a consultant and speaker for the non-product health topics series on relationship centred care for Merck & Co.
To cite: Woz S, Mitchell S, Hesko C, et al. Gender as Risk factor for 30 days post-discharge hospital utilisation: a secondary data analysis. BMJ Open 2012;2:e000428. doi:10.1136/bmjopen-2011-000428
Contributors SW was responsible for conception, design, acquisition of data, analysis and interpretation of results. She also made significant contributions to the drafting of the manuscript and revising for intellectual content and final approval of published version. SM was responsible for the analysis and interpretation of the results and made significant contributions to the drafting of the manuscript, its intellectual content and final approval of published version. CH was responsible for conception, design and acquisition of data and analysis and interpretation of the data. She contributed to the intellectual content of the manuscript and was responsible for approval of the final version of the article. MP was responsible for conception and design and analysis and interpretation of data. He also contributed significantly to the critical revisions of the manuscript and final approval of the submitted version. JG was responsible for conception and design and analysis and interpretation of data. He also contributed significantly to the critical revisions of the manuscript and final approval of the submitted version. VKC was responsible for conception and design, data analysis and interpretation, drafting of the manuscript and approval of the final version. JO was responsible for design, data collection, analysis and interpretation, drafting of the manuscript and final approval of published version. BJ was responsible for conception and design and analysis and interpretation of data. He also contributed significantly to the critical revisions of the manuscript and final approval of the submitted version.
Funding This project was supported by the Agency for Healthcare Research and Quality grants 1UC1HS014289-01 and 1U18HS015905-01 (BJ) and National Heart, Lung, and Blood Institute, National Institutes of Health, grant 1 R01 HL081307-01 (BJ).
Competing interests None.
Ethics approval Ethics approval was approved by the Boston University Internal Review Board.
Provenance and peer review Not commissioned; externally peer reviewed.
Data sharing statement No unpublished data are available.
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