Wachterman MW, Marcantonio ER, Davis RB, McCarthy EP. Association of Hospice Agency Profit Status With Patient Diagnosis, Location of Care, and Length of Stay. JAMA. 2011;305(5):472-479. doi:10.1001/jama.2011.70
Author Affiliations: Division of General Medicine and Primary Care (Drs Wachterman, Davis, and McCarthy), Divisions of General Medicine and Primary Care and Gerontology (Dr Marcantonio), Department of Medicine, Beth Israel Deaconess Medical Center, Harvard Medical School, Boston, Massachusetts.
Context Medicare's per diem payment structure may create financial incentives to select patients who require less resource-intensive care and have longer hospice stays. For-profit and nonprofit hospices may respond differently to financial incentives.
Objective To compare patient diagnosis and location of care between for-profit and nonprofit hospices and examine whether number of visits per day and length of stay vary by diagnosis and profit status.
Design, Setting, and Patients Cross-sectional study using data from the 2007 National Home and Hospice Care Survey. Nationally representative sample of 4705 patients discharged from hospice.
Main Outcome Measures Diagnosis and location of care (home, nursing home, hospital, residential hospice, or other) by hospice profit status. Hospice length of stay and number of visits per day by various hospice personnel.
Results For-profit hospices (1087 discharges from 145 agencies), compared with nonprofit hospices (3618 discharges from 524 agencies), had a lower proportion of patients with cancer (34.1%; 95% CI, 29.9%-38.6%, vs 48.4%; 95% CI, 45.0%-51.8%) and a higher proportion of patients with dementia (17.2%; 95% CI, 14.1%-20.8%, vs 8.4%; 95% CI, 6.6%-10.6%) and other noncancer diagnoses (48.7%; 95% CI, 43.2%-54.1%, vs 43.2%; 95% CI, 40.0%-46.5%; adjusted P < .001). After adjustment for demographic, clinical, and agency characteristics, there was no significant difference in location of care by profit status. For-profit hospices compared with nonprofit hospices had a significantly longer length of stay (median, 20 days; interquartile range [IQR], 6-88, vs 16 days; IQR, 5-52 days; adjusted P = .01) and were more likely to have patients with stays longer than 365 days (6.9%; 95% CI, 5.0%-9.4%, vs 2.8%; 95% CI, 2.0%-4.0%) and less likely to have patients with stays of less than 7 days (28.1%; 95% CI, 23.9%-32.7%, vs 34.3%; 95% CI, 31.3%-37.3%; P = .005). Compared with cancer patients, those with dementia or other diagnoses had fewer visits per day from nurses (0.50 visits; IQR, 0.32-0.87, vs 0.37 visits; IQR, 0.20-0.78, and 0.41 visits; IQR, 0.26-0.79, respectively; adjusted P = .002) and social workers (0.15 visits; IQR, 0.07-0.31, vs 0.11 visits; IQR, 0.04-0.27, and 0.14 visits; IQR, 0.07-0.31, respectively; adjusted P < .001).
Conclusion Compared with nonprofit hospice agencies, for-profit hospice agencies had a higher percentage of patients with diagnoses associated with lower-skilled needs and longer lengths of stay.
During the past 10 years, the for-profit hospice sector has increased substantially.1 From 2000 to 2007, the number of for-profit hospices more than doubled from 725 to 1660, while the number of nonprofit hospices remained essentially the same—1193 in 2000 and 1205 in 2007.2 Overall, for-profit hospices have significantly higher profit margins than nonprofit hospices, varying from 12% to 16% between 2001 and 2004, compared with −2.9% and −4.4% for nonprofit hospices.2 This rapid increase in the for-profit hospice sector and the differential profit margins have raised questions about potential financial incentives in hospice reimbursement.
Medicare payment policy is a key determinant of hospice reimbursement. Medicare beneficiaries compose 84% of patients in hospice,3 and about 40% of Medicare decedents use hospice annually.2 Medicare reimburses hospices a per diem rate ($142.91/d in 2010) for routine care, which can be provided at home or in a nursing home.3 This capitated rate is fixed regardless of the care needs of individual patients or the services that they receive and may create a financial incentive to select patients requiring less resource-intensive services. Moreover, longer hospice stays are thought to be more profitable than shorter stays,2,4 and emerging evidence suggests that hospice costs tend to be U-shaped with considerable fixed costs at the time of enrollment and again near death.5- 8 Thus, hospices can reduce their average daily costs by attracting patients with longer lengths of stay (LOS).7,9 Some data suggest that for-profit hospices are less likely to admit patients with shorter expected LOS,10 while other data suggest no difference in mean LOS between for-profit and nonprofit hospices.11 The Balanced Budget Act of 1997 relaxed the previous 210-day cap on Medicare hospice coverage, allowing for an unlimited number of 60-day periods, provided patients are recertified (ie, deemed to have 6 months or less to live if their disease runs its normal course).2 This policy change allowed for longer reimbursable stays in hospice and may have contributed to the rise of for-profit hospices.
In this context, we compared patient diagnosis and location of care between for-profit and nonprofit hospices and examined whether LOS and the number of visits per day by hospice personnel vary by diagnoses and by profit status.
We examined a nationally representative sample of patients discharged from hospice, primarily due to death (84%), using the 2007 National Home and Hospice Care Survey (NHHCS).12 The 2007 NHHCS used a stratified 2-stage sampling design. A representative sample of US home health and hospice care agencies was selected after being stratified by agency type and metropolitan statistical area. From more than 15 000 agencies, 1545 agencies were randomly sampled from the strata with probability proportional to size. Overall, 1461 selected agencies were eligible (95%), and 1036 agreed to participate (unweighted, 71%; weighted, 59%).13
A computer algorithm randomly selected up to 10 current patients per home health agency, up to 10 hospice discharges per hospice agency, or a combination of up to 10 current home health patients and hospice discharges for a mixed agency. Hospice discharges during the 3-month period before the agency interview were eligible. Our study focused solely on the sample of 4733 patients discharged from hospice. We excluded 28 discharges with any missing data on our main factors of interest (LOS, diagnosis, and location of care). Our final sample consisted of 4705 hospice discharges.
Data were collected through in-person interviews with the hospice staff member who knew each sampled patient best; questions were answered in consultation with the patient's medical record or other records. No patients or family members were interviewed. This study was deemed exempt by the Beth Israel Deaconess Medical Center institutional review board because we used publicly available deidentified data.
Hospice profit status was obtained from the agencies' administrators. The agency was considered for-profit if it was owned by an individual, partnership, or corporation and nonprofit if owned by a nonprofit organization, religious group, or government agency.
We classified patients' primary admission diagnoses into the following 3 groups using codes from the International Classification of Diseases, Ninth Revision, Clinical Modification: cancer (140-239), dementia (290.0, 290.42, 294.8, 294.9, 331.0, 331.11, 331.4, 331.82, and 331.9), and other (all remaining codes, such as congestive heart failure). We categorized location of care as home, nursing home, hospital, residential hospice, or other. Length of stay was measured from date of hospice enrollment until discharge or death, whichever came first. We also assessed LOS in categories of less than 7 days, 7 to 30 days, 31 to 180 days, 181 to 364 days, and 365 days or longer. We measured number of visits per day by each of the following hospice personnel: nurses, social workers, and home health aides. We computed each measure by dividing the total number of visits by the patient's LOS.
We used the following demographic characteristics as covariates: age at hospice entry (<50 y, 50-64 y, 65-74 y, 75-84 y, 85-89 y, ≥90 y), sex, race/ethnicity (non-Hispanic white, non-Hispanic black, Hispanic, other), marital status (married/partnered, not married), primary payment source (Medicare, Medicaid, private, other), and presence of a primary caregiver (yes/no). The NHHCS collected race/ethnicity data using predetermined categories through interviews with the hospice staff members who knew the participants.
The available clinical characteristics other than diagnosis included the number of activities of daily living needing assistance (eating, bathing, dressing, toileting, transferring: categorized as 0, 1-3, 4, or all 5) and mobility impairment (required no assistance, required assistance with walking, and did not walk). Data were only available for 2 agency characteristics other than profit status: whether the hospice agency was part of a chain (yes/no) and metropolitan statistical area, defined by the US Census as metropolitan (at least 1 urban area with a population ≥50 000), micropolitan (an area with a population of 10 000-49 999), or “neither,” eg, rural (did not meet criteria for metropolitan or micropolitan).
All analyses were performed using SAS-callable SUDAAN version 10 (RTI International, Research Triangle Park, North Carolina) to account for the complex sampling design. Data were weighted to reflect national estimates of hospice discharges. We report weighted percentages with corresponding 95% confidence intervals (CIs). Statistical tests were 2-sided.
We used Pearson χ2 tests and t tests to examine the association between profit status and patient and agency characteristics, hospice LOS, and number of visits per day. We used log transformation for our outcomes of LOS and number of visits per day to approximate normal distributions and fit unadjusted linear regression models to examine the association between profit status and each outcome. For patients with no visits of a particular type, we imputed a visit rate of 0.5 divided by the patient's LOS to avoid taking the logarithm of zero. We then repeated these analyses stratifying by diagnosis to assess differences by profit status within each diagnosis group. We further assessed whether number of visits per day varied by categories of LOS.
We used logistic regression to determine whether diagnosis and location of care were independent correlates of having been in a for-profit vs nonprofit hospice after adjusting for demographic, clinical, and agency covariates. We used linear regression to examine the association between profit status and log(LOS) adjusted for all covariates, including diagnosis and location of care. We used linear regression models to examine differences in number of visits per day by profit status and diagnosis after adjustment. To determine whether the association between diagnosis and number of visits per day varied by profit status, we used the Wald χ2 test to further assess the interaction between profit status and diagnosis group. We performed similar multivariable analyses to examine differences in number of visits per day by profit status and LOS categories.
All statistical testing was 2-sided. Our 3 main factors of interest (profit status, diagnosis, and location of care) were defined a priori, and our study was considered hypothesis generating rather than definitive testing. However, we did calculate a Bonferroni-corrected critical value of P < .017, given our 3 factors of interest.
Our sample included 4705 patients discharged from hospice in 2007, of which 1087 patients (30.7%) were discharged from 145 for-profit agencies and 3618 patients (69.3%) were discharged from 524 nonprofit agencies. Our sample was representative of an estimated 1.03 million patients discharged from hospice in 2007. Table 1 presents characteristics by agency profit status. Patients from for-profit and nonprofit hospices were similar except that those from for-profit hospices compared with nonprofit hospices were more likely to be non-Hispanic black (10.6%; 95% CI, 7.0%-15.8%, vs 6.4%; 95% CI, 4.7%-8.7%, respectively) or Hispanic (7.5%; 95% CI, 4.5%-12.3%, vs 2.7%; 95% CI, 1.8%-4.1%; P = .02). For-profit agencies compared with nonprofit agencies were also more likely to be part of a chain (74.0%; 95% CI, 61.1%-83.7%, vs 5.9%; 95% CI, 3.5%-9.8%, respectively; P < .001).
Table 2 demonstrates that diagnosis and location of care both varied by profit status. Compared with nonprofit hospices, for-profit hospices had a lower proportion of patients with cancer (48.4%; 95% CI, 45.0%-51.8%, vs 34.1%; 95% CI, 29.9%-38.6%, respectively) and higher proportions of patients with dementia (8.4%; 95% CI, 6.6%-10.6%, vs 17.2%; 95% CI, 14.1%-20.8%) and other diagnoses (43.2%; 95% CI, 40.0%-46.5%, vs 48.7%; 95% CI, 43.2%-54.1%). These differences remained significant after adjustment (P < .001). Compared with nonprofit hospices, for-profit hospices also had a higher proportion of patients residing in nursing homes (23.1%; 95% CI, 20.4%-26.1%, vs 34.2%; 95% CI, 27.9%-41.0%, respectively) and a lower proportion residing at home (57.1%; 95% CI, 53.5%-60.7%, vs 51.5%; 95% CI, 44.6%-58.3%). However, there was no independent association of location of care with profit status after adjustment for all covariates, most notably diagnosis.
Reasons for discharge among for-profit hospices and nonprofit hospices were, respectively, death (77.7% vs 87.3%), condition stabilized or improved (6.7% vs 4.3%), obtained more aggressive therapy (7.7% vs 3.2%), moved to a different geographic region (2.3% vs 1.6%), and other reasons (5.2% vs 3.5%). Also, for-profit hospices had a higher proportion of discharges based on readmissions than nonprofit hospices (9.3% vs 5.5%, respectively).
Table 3 presents the median LOS in hospice with corresponding 25th and 75th percentiles by profit status of all patients and stratified by diagnosis. Median LOS was 4 days longer in for-profit hospices as compared with nonprofit hospices (20 days; interquartile range, [IQR], 6-88, vs 16 days; IQR, 5-52; P = .002). The unadjusted LOS was 41.0% longer (95% CI, 13.5%-75.1%) in for-profit hospices vs nonprofit hospices. After full adjustment, LOS remained significantly longer in for-profit hospices compared with nonprofit hospices (26.2%; 95% CI, 4.9%-51.9%; P = .01). A model adjusting for only diagnosis and location of care was nearly identical, suggesting that these 2 factors account for most of the variation in LOS.
Compared with nonprofit hospices, median LOS in for-profit hospices was similar for patients with cancer (16 days; IQR, 6-39, vs 15 days; IQR, 6-44, respectively) and longer for patients with dementia (26 days; IQR, 6-135, vs 43 days; IQR, 10-161) and other noncancer diagnoses (14 days; IQR, 4-70, vs 23 days; IQR, 6-100). In adjusted analyses, patients with dementia had longer median LOS than patients with cancer and other diagnoses (35 days; IQR, 7-161, vs 16 days; IQR, 6-40, and 17 days; IQR, 4-85, respectively; P < .001). Compared with patients in nonprofit hospices, patients in for-profit hospices were more likely to have stays longer than 365 days (2.8%; 95% CI, 2.0%-4.0%, vs 6.9%; 95% CI, 5.0%-9.4%) and were less likely to have stays less than 7 days (34.3%; 95% CI, 31.3%-37.3%, vs 28.1%; 95% CI, 23.9%-32.7%; P = .005).
Table 4 presents the median number of visits per day by nurses, social workers, and home health aides overall and stratified by diagnosis. Overall, for-profit and nonprofit hospices provided similar numbers of nursing visits per day (0.45 visits; IQR, 0.27-0.82, vs 0.45 visits; IQR, 0.28-0.83, respectively). However, for-profit hospice agencies compared with nonprofit agencies provided fewer social work visits per day (0.12 visits; IQR, 0.06-0.25, vs 0.15 visits; IQR, 0.07-0.34; unadjusted P = .006; adjusted P = .03) and more home health aide visits per day (0.33 visits; IQR, 0.15-0.50, vs 0.25 visits; IQR, 0.07-0.45; unadjusted P = .004; adjusted P = .02). Compared with cancer patients, those with dementia or other diagnoses had fewer visits per day from nurses (0.50 visits; IQR, 0.32-0.87, vs 0.37 visits; IQR, 0.20-0.78, and 0.41 visits; IQR, 0.26-0.79, respectively; adjusted P = .002) and social workers (0.15 visits; IQR, 0.07-0.31, vs 0.11 visits; IQR, 0.04-0.27, and 0.14 visits; IQR, 0.07-0.31, respectively; adjusted P < .001). No significant interaction was observed between diagnosis and hospice profit status for any of the types of visits examined. Table 5 presents the median number of visits per day by each personnel type, stratified by LOS categories. Although patients with stays less than 7 days had more visits per day by nurses and social workers than patients with longer stays, this did not differ by profit status.
The recent increase in the for-profit hospice sector raises critical questions about potential financial incentives in hospice reimbursement. Using nationally representative data, we found notable differences in the types of patients enrolled in for-profit hospices compared with nonprofit hospices. For-profit hospices had a disproportionate number of patients with noncancer diagnoses, dementia in particular. For-profit hospices also had a greater proportion of patients with prolonged LOS (≥365 days).
We also found that patients with noncancer diagnoses and those with prolonged LOS received fewer visits per day from skilled personnel (ie, nurses and social workers). Despite these differences in case mix, we found that patients received similar rates of nursing visits regardless of hospice profit status. On the other hand, patients in for-profit hospices received fewer social work visits and more home health aide visits per day than those in nonprofit hospices as would be expected given the observed case-mix differences. Our findings have potentially important implications both for clinicians taking care of patients at the end of life and for policy makers in the area of Medicare hospice payment.
The current Medicare Hospice Benefit reimburses hospices at a fixed per diem rate that does not consider the patient's diagnosis, location of care, or hospice LOS. Under this system, profit can be maximized by caring for patients with certain diagnoses that require fewer skilled services, patients residing in nursing homes, or patients with longer hospice stays.2,4,6,10,14 Although other studies have found that patients with noncancer diagnoses were significantly more likely than cancer patients to be in for-profit hospices,10,11 we further examined the subset of patients with dementia and found that they were even more likely to be enrolled in for-profit hospices. Our findings indicate that approximately two-thirds of patients in for-profit hospices have dementia and other noncancer diagnoses, whereas only about half of patients in nonprofit hospices have these diagnoses.
We also found that these diagnoses were associated with longer stays in hospice, which are known to be more profitable, and that overall patients with these diagnoses had fewer visits per day by skilled personnel (nurses and social workers ), which could be financially advantageous for hospices under a capitated reimbursement system. For-profit hospices were also less likely than nonprofit hospices to have patients enrolled for fewer than 7 days, and these patients had more visits from skilled personnel, which is costly for hospices. Our findings build on previous research that has shown that LOS in hospice and services delivered correlate with patients' terminal diagnoses.7,15,16
Previous studies examining the association of profit status or diagnosis with LOS or care intensity have used proprietary data5,7 or data limited to a single state.11,17 Lorenz et al11 used 1997 California data to show that 46% of patients in for-profit hospices had noncancer diagnoses, compared with 28% in nonprofits. We find a similar difference, although of smaller magnitude—which may be partially due to the fact that our 2007 data show a substantial increase in noncancer diagnoses in both for-profit and nonprofit hospices, compared with their 1997 study.11 Our study also examined dementia specifically and demonstrated an even stronger association between profit status and dementia. Another study,18 which used an earlier version of the NHHCS, could only document whether patients had ever received services from a given type of provider because it lacked information on the frequency of visits. Our study, using the most recent NHHCS, expands on prior work by quantifying the number of visits per day delivered by core members of the hospice team and thus provides an improved, albeit imperfect, measure of care intensity. Our study also builds on a study of nursing home patients in a for-profit hospice that found that cancer patients received more visits than noncancer patients.5
For-profit hospices had significantly more patients with stays exceeding 365 days and fewer patients with stays less than 7 days. Although hospice is intended for patients with a prognosis of less than 6 months, research demonstrates19- 22 that it is difficult for clinicians to prognosticate, especially for patients with noncancer diagnoses. Therefore, stays that exceed 6 months may have been appropriate at the time of enrollment. While it is unknown whether hospice patients with stays exceeding 1 year were enrolled inappropriately early in the course of their illnesses, these admissions can be particularly lucrative for hospices in a per diem reimbursement system because, as we found, they receive fewer visits per day from skilled hospice personnel.
Our study has several important limitations. First, the NHHCS includes only patients who were discharged from hospice and therefore underestimates LOS because patients with longer LOS have a lower likelihood of having been discharged and are therefore underrepresented in the sample. Nonetheless, we found that for-profit hospices were more likely than nonprofit hospices to have prolonged LOS (ie, >1 year). This undersampling of long LOS means that our study on the whole probably underestimates the differences in median LOS by profit status.
Second, we lacked data on important agency characteristics beyond metropolitan statistical area and chain status, such as the hospices' geographic location, which may explain the observed differences in racial composition. We also do not know whether hospices were part of a larger system of care, which could facilitate coordination of and transitions in care and thus increase hospice LOS. Third, we lacked data on costs and revenue, and therefore, we do not demonstrate that differences in the diagnostic composition of hospices resulted in lower costs or greater revenue. Fourth, diagnosis is an imperfect measure of disease severity.
Finally, and perhaps most importantly, we are unable to assess the relationship between profit status and quality of care. While our study improves on previous research by assessing the number of visits per day by various hospice personnel, we lacked important information on the length of each visit and care provided. For example, we could not distinguish between a home health aide visit that consisted of a 5-minute “check-in” and a half-day visit providing assistance with activities of daily living. We are also unable to determine whether higher rates of home health aide visits in for-profit hospices reflect additional care or substitution of other types of unmeasured (and potentially more expensive) clinical services. We also could not distinguish between visits delivered by registered nurses and licensed vocational nurses; past research11,17 suggests that registered nurses, who are more skilled and more expensive, deliver a lower proportion of nursing visits in for-profit hospices vs nonprofit hospices.
Clinicians caring for patients considering hospice can be reassured that for-profit hospices appear to provide as many nursing visits and more home health aide visits (although fewer social work visits) than nonprofit hospices. However, there are important policy implications if hospice agencies differentially enroll more patients with dementia and other noncancer diagnoses, who require fewer visits from skilled personnel such as nurses and social workers. Patient selection of this nature leaves nonprofit hospice agencies disproportionately caring for the most costly patients—those with cancer and those tending to begin hospice very late in their course of illness; as a result, those hospices serving the neediest patients may face difficult financial obstacles to providing appropriate care in this fixed per-diem payment system.
Our findings are timely, complement the findings of the Medicare Payment Advisory Committee (MedPAC) reports,2,16 and can help inform the current debate around payment reform in the Medicare Hospice Benefit. MedPAC has recommended that, as of 2013, reimbursement rates for hospice reflect a U-shaped pattern that considers the intensity of care required at the beginning and end of hospice, with higher per diem rates during the first 30 days of enrollment and a standard payment at the time of death. Given that approximately 1 million Medicare beneficiaries use hospice each year and that the for-profit hospice industry continues to expand rapidly, future research is needed to understand more fully the association of profit status with quality of care and patient and caregiver experiences at the end of life.
Corresponding Author: Melissa W. Wachterman, MD, MPH, Beth Israel Deaconess Medical Center, 330 Brookline Ave, Boston, MA 02115 (firstname.lastname@example.org).
Author Contributions: Dr Wachterman had full access to all of the data in the study and takes responsibility for the integrity of the data and the accuracy of the data analysis.
Study concept and design: Wachterman, McCarthy.
Acquisition of data: Wachterman, McCarthy.
Analysis and interpretation of data: Wachterman, Marcantonio, Davis, McCarthy.
Drafting of the manuscript: Wachterman, McCarthy.
Critical revision of the manuscript for important intellectual content: Wachterman, Marcantonio, Davis, McCarthy.
Statistical analysis: Wachterman, Davis, McCarthy.
Obtained funding: Wachterman.
Administrative, technical, or material support: Wachterman, Marcantonio, Davis, McCarthy.
Study supervision: Marcantonio, McCarthy.
Conflict of Interest Disclosures: All authors have completed and submitted the ICMJE Form for Disclosure of Potential Conflicts of Interest and none were reported.
Funding/Support: Dr Wachterman received support from grant 6T32HP12706-02-01 from the Health Resources and Services Administration of the Department of Health and Human Services to support the Harvard Medical School Fellowship Program in General Medicine and Primary Care.
Role of the Sponsor: The funding organization had no role in the design and conduct of the study; in the collection, analysis, and interpretation of the data; or in the preparation, review, or approval of the manuscript.
Previous Presentation: An earlier version of this work was presented at the national meeting of the Society of General Internal Medicine; Minneapolis, Minnesota; April 30, 2010; and at the national meeting of Academy Health; Boston, Massachusetts; June 28, 2010.
Disclaimer: The study contents are solely the responsibility of the authors and do not necessarily represent the official views of the Department of Health and Human Services.
Additional Contributions: We thank Benjamin Sommers, MD, PhD, Harvard School of Public Health, for his editing assistance and helpful comments on the manuscript. He did not receive compensation for the contribution.