Background
In Canada, formal or publically provided home care has been identified as an important component of the health care system [1]. In 2012, nearly 2.2 million Canadians received help or care at home because of a long-term health condition, disability, or problems related to aging [2]. The provision of formal home care services has the potential to significantly reduce utilization of acute care services and delay long-term care (LTC) admission [3‐5]. An important public health priority is evaluating possible approaches to identifying those clients most at-risk of adverse health outcomes [6‐8] to facilitate targeted interventions within this population [9, 10].
The concept of frailty offers a promising avenue for identifying and targeting care to home care clients at risk of a decline in their health and/or functional status [9‐11]. Frailty is a state of heightened vulnerability to stressors due to cumulative decline across multiple physiological systems [11, 12]. Although frailty research on home care clients is relatively scarce, community-based studies indicate that the prevalence of frailty increases with advancing age (to over 30 % among those aged 85 and older) and is more common among women [12‐16]. Frailty is also a significant predictor of disability, hospitalization, and mortality independent of measures of comorbidity [12‐14, 17].
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A number of approaches to screen for frailty and/or grade it have been proposed with no consensus on which one to use [18‐20]. One of the most commonly used approaches involves the calculation of a Frailty Index (FI) based on a count of accumulated health deficits (i.e., symptoms, signs, diseases, disabilities, and/or laboratory abnormalities) divided by the number of potential deficits considered in a given individual [21]. In deriving a FI measure, typically 30 or more health “deficits” are selected that meet the following criteria: (i) they are associated with health status; (ii) cover a range of systems/domains (e.g., physical, cognitive, psychosocial); and (iii) increase with age but do not saturate (become universal) at older ages. Demonstrating the feasibility of deriving a frailty measure like the FI from routinely collected data, as well as its clinical utility, is appealing given the potential to inform research, care and health system planning for home care clients at a population level.
FI measures have been calculated for older adults receiving care in both assisted living [22, 23] and home care settings [24] using items derived from a standardized, comprehensive clinical assessment, the Resident Assessment Instrument (RAI). As might be expected given the flexibility in selecting items for a FI, there was variation across these studies in the number and range of the specific deficits or items included [22, 24]. Another approach to the detection of frailty based on RAI data is the Changes in Health, End-stage disease and Signs and Symptoms (CHESS) scale [25, 26]. Higher scores on the CHESS scale have been shown to predict mortality and hospitalization among home care recipients, as well as residents of assisted living and LTC facilities [22, 24, 25, 27]. Although these different approaches to identifying frailty might reasonably be expected to capture distinct subgroups of vulnerable clients, with varying implications for clinical or social care and interventions, few studies have directly compared different measures in terms of their descriptive characteristics or predictive validity for major health outcomes in older adults.
In our previous assisted living study [22], we showed that two FI measures (varying in item number and domains covered) and the CHESS scale modestly improved the performance of predictive models for mortality and LTC placement. The more comprehensive FI, comprised of 83 items covering a diverse range of domains, performed significantly better than the other approaches in predicting institutionalization [22]. Using RAI data available for a large sample of older home care clients in Ontario, Armstrong et al. [24] found that higher frailty levels as defined by three measures, including the CHESS scale and a 50 item FI were associated with a greater risk of a composite adverse outcome (i.e., death or institutionalization). Although informative, both studies present limitations in generalizing to a broader home care population. With our previous study, it is important to note the differences between residents of assisted living facilities and home care clients in sociodemographic and functional characteristics and in their care settings, staff and service availability [22‐24]. The study by Armstrong et al., [24] evaluated clients from select catchment areas only, employed a less comprehensive FI measure, and limited their analysis to a single composite outcome.
To address these limitations, we utilized population-based linked administrative health and RAI data for a cohort of older home care clients in Ontario, to: (i) determine the prevalence and correlates of frailty in a home care population as operationally defined by two versions of a FI and CHESS scale; (ii) examine the agreement between these measures; and, (iii) compare the relative associations of these three measures (and their predictive validity) with death, institutionalization, and hospitalization (including alternate level of care bed stay) during one year of follow-up.
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Methods
Study design, setting, and population
We conducted a retrospective, population-based cohort study of long-stay home care clients by linking Resident Assessment Instrument for Home Care (RAI-HC) data with multiple health administrative datasets from Ontario, Canada. These datasets were linked using unique encoded identifiers and analyzed at the Institute for Clinical Evaluative Sciences.
Ontario has a diverse, multicultural population of approximately 13 million people with nearly all residents eligible for medically necessary physician and hospital services in the publicly funded health care system. In addition, a variety of community and mental health services, a portion of the cost of care in LTC facilities, and most of the cost of prescription drugs for individuals aged 65 years and older, people on social assistance, and Ontario residents facing high drug costs are also provided through the publicly funded system. Access to home care services is centrally managed through 14 regional coordination centres (Community Care Access Centres) across the province [28]. Services are provided on a short- or long-stay basis with the latter referring to clients receiving ongoing supportive care for more than 60 days in a single episode. In Ontario, the RAI-HC assessment is only mandatory for all long-stay clients [6, 7, 29].
The RAI-HC and the home care service use databases were used to identify all long-stay home care clients assessed between April 2010 and March 2013. The RAI-HC is administered by trained professionals and provides a standardized assessment of clients’ physical and cognitive status, health conditions, behavioural problems, medications, and service utilization [30, 31]. Previous work has shown support for the reliability and validity of the RAI home care tool [31]. For individuals with multiple assessments, we utilized information from their earliest assessment during the study period (index date). We excluded clients aged <66 years or >105 years, those receiving home care for case management purposes only, individuals with a prior LTC stay, individuals who died on or prior to cohort entry, and clients with a non-Ontario postal code.
Ethics approval was obtained from the University of Waterloo Research Ethics Committee and the Research Ethics Board of Sunnybrook Health Sciences Centre, Toronto, Ontario, Canada.
Frailty measures
Three separate measures of frailty were examined in our cohort. Two FI measures, a full FI based on the 83-item measure developed by Hogan et al. [22] using the approach of Searle and colleagues [21] and a modified FI modeled on the original 50-item measure developed by Armstrong et al. [24] were calculated. Both indices were derived from automated and previously collected clinical assessment data (available from the RAI-HC) and were calculated as the proportion of accumulated to potential health deficits. Our methodological and conceptual approach to developing the two FI measures was consistent with our previous assisted living study [22]. Due to minor differences across versions of the RAI tools, the adapted full FI and modified FI included 72 and 48 items respectively (see Additional file 1: Table S1). Items with a missing value were removed from both the numerator and denominator when calculating either frailty index for an individual participant. For both Frailty Indices, clients were categorized as ‘robust’ (FI values <0.2), ‘pre-frail’ (values between 0.2–0.3), and ‘frail’ (values >0.3) in accordance with previous studies [21, 22, 32].
The CHESS scale, a health instability measure embedded within the RAI-HC tool, was used as our final frailty measure. CHESS scale values range from 0 to 5, with a score of 0 representing low health instability and a score of 5 representing high health instability. As in previous studies, clients were categorized as ‘robust’ (CHESS score of 0), ‘pre-frail’ (CHESS score of 1), and ‘frail’ (CHESS score of 2 or more) [22].
Study outcomes
Outcomes of interest were death, LTC placement, inpatient hospitalization, and hospitalization with an alternate level of care (ALC) bed stay [see below for an explanation of this term] in the year following the index date. Mortality data were ascertained from the Registered Persons Database (RPDB), which contains basic demographic information for residents eligible to receive publicly-funded health services in Ontario. Admissions to LTC facilities were determined using the Continuing Care Reporting System Long Term Care (CCRS-LTC) database, which captures admission and RAI assessment information on Ontario LTC residents. The Canadian Institute of Health Information’s Discharge Abstract Database (CIHI-DAD) was used to identify all hospitalizations. The CIHI-DAD contains detailed administrative information that permitted the measurement of hospital visits requiring an ALC stay. ALC patients are those who no longer require hospital services, but cannot be discharged because appropriate care is not available elsewhere [6, 33].
Baseline characteristics
Using the RPDB, we determined each client’s age, sex, and Rurality Index of Ontario (RIO) score. The RIO score is a continuous measure of remoteness that accounts for community size and travel time to basic and advanced medical services [34], and clients were categorized into Rural (RIO score ≥40), Urban (RIO score 10–39), and Major Urban (RIO score 0–9) areas.
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The Ontario Drug Benefit (ODB) database contains prescription medication claims for those covered under the provincial drug program, mainly those aged 65 years and older. We used the ODB database to count the number of unique prescription medications dispensed which overlapped the index date. Hospital and emergency department use in the year prior to index date was enumerated using CIHI-DAD and National Ambulatory Care Reporting System (NACRS), respectively. A general measure of comorbidity, the number of Adjusted Diagnosis Groups (ADGs) categories, was derived using the Johns Hopkins Adjusted Clinical Group Case-Mix System and based on diagnostic information from health services use in the 2 years prior to the index date [35]. We also derived marital status and measures of caregiver availability, support, and distress from assessment items in the RAI-HC tool.
Statistical analysis
For each frailty measure, we compared the baseline characteristics between ‘robust’, ‘pre-frail’, and ‘frail’ individuals using one-way analysis of variance for continuous variables and chi-square tests for categorical variables. Note, for ease of presentation, descriptive data for the full FI is presented in the main manuscript with comparable data for the modified FI and CHESS provided in the Additional file 1. A weighted Kappa statistic was used to assess the agreement between the full FI, the modified FI, and the CHESS scale using a 3-level risk categorization [36]. All outcomes were treated as binary variables (e.g., occurred or did not occur during the year of follow-up). We examined the unadjusted and adjusted associations between the three frailty measures and our study outcomes, separately, using log-binomial regression models to estimate risk ratios. Adjusted models controlled for age, sex, and general comorbidity measured using ADG groupings. We restricted our covariates to age, sex, and comorbidity to facilitate comparisons with previous research [22] and because of the need to adopt a parsimonious approach to modeling given that other potential covariates are already captured by the FI. For all frailty measures, those defined as ‘robust’ served as the reference category. When examining hospitalizations with an ALC stay, those hospitalized without an ALC stay (N = 66,764) were removed from the analysis.
To compare the predictive validity for each frailty measure in relation to our study outcomes, we calculated the area under the receiver operating characteristic curve (AUC) for a model that included age, sex, and comorbidity, and for models that included age, sex, comorbidity, and each frailty measure separately. Using the nonparametric approach proposed by Delong [37], we calculated the p-values comparing the AUC of each respective model to the reference model that included age, sex, comorbidity, and the full FI.
All statistical tests were 2-tailed and we defined P < 0.05 as the level of statistical significance. Analyses were conducted using SAS Enterprise Guide, Version 6.1 (SAS Institute, Inc.).
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Results
We identified 296,964 long-stay home care clients assessed between April 2010 and March 2013. Clients aged <66 years or >105 years (N = 55,367; 18.6 %), those receiving home care exclusively for case management purposes (N = 4444; 1.5 %), previous LTC residents (N = 2351; 0.8 %), those who died on or prior to cohort entry (N = 183; 0.06 %), or clients with a non-Ontario postal code (N = 67; 0.02 %) were excluded.
In the cohort analyzed (N = 234,552 long-stay home care clients), 19.5 % (95 % Confidence Interval [CI] 19.3–19.7), 24.4 % (95 % CI 24.2–24.6), and 44.1 % (95 % CI 43.9–44.3) were categorized as frail using the full FI, modified FI, and CHESS scale, respectively (Table 1). The prevalence of frailty was 19.3 % (95 % CI 19.1–19.5), 24.0 % (95 % CI 23.8–24.2), and 43.2 % (95 % CI 42.9–43.4) among women and 19.9 % (95 % CI 19.6–20.2), 25.2 % (95 % CI 24.9–25.5), and 45.9 % (95 % CI 45.6–46.2) among men when using the full FI, modified FI, and CHESS scale, respectively (data not shown). The distribution of the continuous versions of the full FI and modified FI are presented in Additional file 1: Figure S1. During the year following assessment, 17.5 % of long-stay home care clients had died, 17.1 % had been admitted to long-term care homes, 42.0 % had at least one acute care hospitalization, and 13.5 % were hospitalized with an ALC stay.
Table 1
Baseline characteristics, frailty status, and study outcomes among long-stay home care recipients in Ontario
Characteristics | Long-stay home care recipients (N = 234,552) |
|---|---|
Sociodemographic characteristics
| |
Age (years), mean ± SD | 82.0 ± 7.42 |
Sex | |
Male | 83,125 (35.4 %) |
Female | 151,427 (64.6 %) |
Rurality Index of Ontario | |
Major Urban | 156,807 (67.2 %) |
Urban | 52,881 (22.7 %) |
Rural | 23,540 (10.1 %) |
Marital status | |
Married | 92,064 (39.3 %) |
Never Married/Other | 11,888 (5.1 %) |
Widowed | 115,176 (49.1 %) |
Separated/Divorced | 15,424 (6.6 %) |
Primary caregiver | |
No primary caregiver | 5,181 (2.2 %) |
Yes, does not live with client | 110,884 (47.3 %) |
Yes, lives with client | 118,487 (50.5 %) |
Caregiver is distressed | 54,620 (23.3 %) |
Total weekday hours of caregiver support during past week, mean ± SD | 11.68 ± 14.06 |
Total weekend hours of caregiver support during past week, mean ± SD | 4.98 ± 5.73 |
Average hours of caregiver support per day, mean ± SD | 2.38 ± 2.78 |
Comorbidity
| |
Number of ADG comorbidity categories | |
0–5 | 32,719 (13.9 %) |
6–9 | 71,578 (30.5 %) |
10+ | 130,255 (55.5 %) |
Health care utilization
| |
Acute care hospitalization in year prior to index date | 106,956 (45.6 %) |
Acute care hospitalization with ALC stay in year prior to index date | 25,870 (11.0 %) |
Emergency department visit in year prior to index date | 160,770 (68.5 %) |
Number of unique prescription medications overlapping index date, mean ± SD | 6.05 ± 3.83 |
Unique prescription medications overlapping index date | |
0–5 | 111,120 (47.4 %) |
6–9 | 81,204 (34.6 %) |
10+ | 42,228 (18.0 %) |
Frailty status
| |
Full Frailty Index [FI] | |
Robust | 108,676 (46.3 %) |
Pre-Frail | 80,155 (34.2 %) |
Frail | 45,721 (19.5 %) |
Modified Frailty Index [FI] | |
Robust | 95,209 (40.6 %) |
Pre-Frail | 82,107 (35.0 %) |
Frail | 57,236 (24.4 %) |
CHESS Scale | |
Robust
| 55,241 (23.6 %) |
Pre-Frail | 75,763 (32.3 %) |
Frail | 103,548 (44.1 %) |
Outcomes
a
one year following index date
| |
Death | 41,044 (17.5 %) |
LTC admission | 40,144 (17.1 %) |
Hospitalization | 98,385 (42.0 %) |
Hospitalization with ALC stay | 31,621 (13.5 %) |
Clients categorized as frail on all three measures were older, received more hours of unpaid caregiver support per week, and were more likely to have unpaid caregivers reporting distress (Table 2 for baseline characteristics by the full FI; Additional file 1: Tables S2 and S3 for characteristics by the modified FI and CHESS scale, respectively). Additionally, frail clients had greater comorbidity as measured by the number of ADG categories than pre-frail and robust individuals, were taking more prescription drugs, and had more hospital admissions and emergency department visits in the year prior to the index date.
Table 2
Baseline characteristics and outcomes for long-stay home care recipients in Ontario, by the full frailty index
Characteristicsa | Full Frailty Index [FI] | P-value | ||
|---|---|---|---|---|
Robust (N = 108,676) | Pre-Frail (N = 80,155) | Frail (N = 45,721) | ||
Sociodemographic characteristics
| ||||
Age (years), mean ± SD | 81.52 ± 7.45 | 82.11 ± 7.33 | 82.94 ± 7.42 | <.001 |
Sex | <.001 | |||
Male | 38,967 (35.9 %) | 27,606 (34.4 %) | 16,552 (36.2 %) | |
Female | 69,709 (64.1 %) | 52,549 (65.6 %) | 29,169 (63.8 %) | |
Rurality Index of Ontario | <.001 | |||
Major Urban | 71,478 (66.1 %) | 53,723 (67.4 %) | 31,606 (69.6 %) | |
Urban | 25,243 (23.3 %) | 17,965 (22.6 %) | 9,673 (21.3 %) | |
Rural | 11,406 (10.5 %) | 7,974 (10.0 %) | 4,160 (9.2 %) | |
Marital status | <.001 | |||
Married | 42,380 (39.0 %) | 31,121 (38.8 %) | 18,563 (40.6 %) | |
Never Married/Other | 6,340 (5.8 %) | 3,658 (4.6 %) | 1,890 (4.1 %) | |
Widowed | 52,399 (48.2 %) | 40,025 (49.9 %) | 22,752 (49.8 %) | |
Separated/Divorced | 7,557 (7.0 %) | 5,351 (6.7 %) | 2,516 (5.5 %) | |
Primary caregiver | <.001 | |||
No primary caregiver | 3,133 (2.9 %) | 1,441 (1.8 %) | 607 (1.3 %) | |
Yes, does not live with client | 54,236 (49.9 %) | 37,256 (46.5 %) | 19,392 (42.4 %) | |
Yes, lives with client | 51,307 (47.2 %) | 41,458 (51.7 %) | 25,722 (56.3 %) | |
Caregiver is distressed | 12,851 (11.8 %) | 21,590 (26.9 %) | 20,179 (44.1 %) | <.001 |
Total weekday hours of caregiver support during past week, mean ± SD | 8.48 ± 9.67 | 12.93 ± 13.92 | 17.10 ± 19.88 | <.001 |
Total weekend hours of caregiver support during past week, mean ± SD | 3.72 ± 4.03 | 5.48 ± 5.67 | 7.09 ± 8.07 | <.001 |
Average hours of caregiver support per day, mean ± SD | 1.74 ± 1.91 | 2.63 ± 2.74 | 3.45 ± 3.93 | <.001 |
Comorbidity
| ||||
Number of ADG comorbidity categories | <.001 | |||
0–5 | 16,855 (15.5 %) | 10,636 (13.3 %) | 5,228 (11.4 %) | |
6–9 | 35,508 (32.7 %) | 23,905 (29.8 %) | 12,165 (26.6 %) | |
10+ | 56,313 (51.8 %) | 45,614 (56.9 %) | 28,328 (62.0 %) | |
Health care utilization
| ||||
Acute care hospitalization in year prior to index date | 46,065 (42.4 %) | 37,250 (46.5 %) | 23,641 (51.7 %) | <.001 |
Acute care hospitalization with ALC stay in year prior to index date | 8,499 (7.8 %) | 9,431 (11.8 %) | 7,940 (17.4 %) | <.001 |
Emergency department visit in year prior to index date | 68,763 (63.3 %) | 56,421 (70.4 %) | 35,586 (77.8 %) | <.001 |
Number of unique prescription medications overlapping index date, mean ± SD | 5.52 ± 3.49 | 6.58 ± 3.89 | 6.39 ± 4.33 | <.001 |
Unique prescription medications overlapping index date | <.001 | |||
0–5 | 58,246 (53.6 %) | 33,155 (41.4 %) | 19,719 (43.1 %) | |
6–9 | 36,256 (33.4 %) | 29,605 (36.9 %) | 15,343 (33.6 %) | |
10+ | 14,174 (13.0 %) | 17,395 (21.7 %) | 10,659 (23.3 %) | |
Outcomes
b
one year following index date
| ||||
Death | 13,212 (12.2 %) | 14,307 (17.8 %) | 13,525 (29.6 %) | <.001 |
LTC admission | 9,372 (8.6 %) | 15,308 (19.1 %) | 15,464 (33.8 %) | <.001 |
Hospitalization | 40,850 (37.6 %) | 35,876 (44.8 %) | 21,659 (47.4 %) | <.001 |
Hospitalization with ALC stay | 11,927 (11.0 %) | 12,205 (15.2 %) | 7,489 (16.4 %) | <.001 |
Between the three frailty measures, the highest level of agreement was between the full FI and the modified FI (agreement = 77.0 %; weighted kappa = 0.72, 95 % CI 0.72–0.73) (Table 3). There was markedly less agreement between either the full FI (weighted kappa = 0.28, 95 % CI 0.28–0.29) or the modified FI (weighted kappa = 0.22, 95 % CI 0.22–0.23) with the CHESS scale.
Table 3
Summary of agreement between frailty measures
Frailty index comparison | Agreement (%) | Weighted Kappa (95 % CI) |
|---|---|---|
Full Frailty Index [FI] - Modified Frailty Index [FI] | 77.0 | 0.72 (0.72–0.73) |
Full Frailty Index [FI] – CHESS scale | 43.9 | 0.28 (0.28–0.29) |
Modified Frailty Index [FI] – CHESS scale | 42.1 | 0.22 (0.22–0.23) |
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For all three frailty measures, clients defined as pre-frail or frail had a greater risk for all study outcomes (death, LTC admission, hospitalization, and hospitalization with ALC stay) compared with robust individuals after adjustment for age, sex and comorbidity (Table 4). The risk ratios for death and LTC admission were larger than those observed for the hospitalization outcomes. When comparing frail with robust individuals, the full FI demonstrated the strongest association with LTC admission (RR = 3.84, 95 % CI 3.75–3.93) while the CHESS scale demonstrated the strongest adjusted associations with hospitalization (RR = 1.34, 95 % CI 1.32–1.36), and hospitalization with ALC stay (RR = 1.62, 95 % CI 1.58–1.67).
Table 4
Associations between frailty measures and outcomes at one year following index date
Frailty index | Model | Frailty levela | Outcomes at one year, risk ratio (95 % CI) | |||
|---|---|---|---|---|---|---|
Death | LTC admission | Hospitalization | Hospitalization with ALC stayb | |||
Full frailty index [FI] | Unadjusted | Pre-Frail | 1.47 (1.44, 1.50) | 2.21 (2.16, 2.27) | 1.19 (1.18, 1.20) | 1.44 (1.41, 1.48) |
Frail | 2.43 (2.38, 2.49) | 3.92 (3.83, 4.01) | 1.26 (1.24, 1.28) | 1.59 (1.55, 1.63) | ||
Adjustedc | Pre-Frail | 1.45 (1.42, 1.48) | 2.20 (2.15, 2.26) | 1.17 (1.16, 1.19) | 1.42 (1.39, 1.45) | |
Frail | 2.32 (2.27, 2.37) | 3.84 (3.75, 3.93) | 1.22 (1.20, 1.23) | 1.51 (1.47, 1.55) | ||
Modified frailty index [FI] | Unadjusted | Pre-Frail | 1.36 (1.33, 1.39) | 2.13 (2.08, 2.19) | 1.16 (1.15, 1.17) | 1.40 (1.37, 1.44) |
Frail | 2.26 (2.22, 2.31) | 3.64 (3.55, 3.73) | 1.25 (1.24, 1.27) | 1.57 (1.53, 1.61) | ||
Adjustedc | Pre-Frail | 1.35 (1.32, 1.38) | 2.11 (2.05, 2.16) | 1.15 (1.14, 1.16) | 1.38 (1.35, 1.41) | |
Frail | 2.16 (2.12, 2.21) | 3.58 (3.50, 3.67) | 1.21 (1.20, 1.23) | 1.50 (1.47, 1.54) | ||
CHESS scale | Unadjusted | Pre-Frail | 1.30 (1.26, 1.34) | 1.39 (1.35, 1.43) | 1.17 (1.15, 1.19) | 1.30 (1.26, 1.34) |
Frail | 2.36 (2.30, 2.43) | 1.96 (1.91, 2.02) | 1.40 (1.38, 1.41) | 1.69 (1.64, 1.74) | ||
Adjustedc | Pre-Frail | 1.29 (1.25, 1.33) | 1.40 (1.36, 1.44) | 1.15 (1.13, 1.17) | 1.28 (1.25, 1.32) | |
Frail | 2.27 (2.21, 2.33) | 1.99 (1.94, 2.04) | 1.34 (1.32, 1.36) | 1.62 (1.58, 1.67) | ||
For all study outcomes, models incorporating measures of frailty in addition to age, sex, and comorbidity had greater AUCs compared with models that included only age, sex, and comorbidity (Table 5). The magnitude of the differences was highest when predicting death and LTC admission (and to a lesser degree in predicting hospitalization with an ALC stay) but relatively lower in models predicting hospitalization. For predicting death, the AUCs were highest for the models incorporating the full FI and the CHESS scale with no significant difference between these two models (p = 0.566). The model incorporating the full FI was a stronger predictor of LTC admission than models utilizing the other frailty measures. For hospitalization, the models including the CHESS scale had significantly higher AUCs, although the incremental gain in AUC compared to models with the other frailty measures was small in absolute terms. The models with the highest AUCs for predicting hospitalization with an ALC stay incorporated either the full FI or the CHESS scale with no significant difference between the two (p = 0.999).
Table 5
Comparison of the area under the receiver operating characteristic curves (AUC) for models using different frailty measures
Outcome | Model predictors | AUC (95 % CI) | P-Value |
|---|---|---|---|
Death | Age, sex, and comorbidity | 0.604 (0.601, 0.607) | <.001 |
Age, sex, comorbidity, and CHESS scale | 0.658 (0.655, 0.660) | 0.566 | |
Age, sex, comorbidity, and modified frailty index | 0.652 (0.649, 0.655) | <.001 | |
Age, sex, comorbidity, and full frailty index | 0.657 (0.654, 0.660) | Reference | |
LTC admission | Age, sex, and comorbidity | 0.573 (0.570, 0.576) | <.001 |
Age, sex, comorbidity, and CHESS scale | 0.617 (0.614, 0.620) | <.001 | |
Age, sex, comorbidity, and modified frailty index | 0.688 (0.685, 0.690) | <.001 | |
Age, sex, comorbidity, and full frailty index | 0.698 (0.695, 0.701) | Reference | |
Hospitalization | Age, sex, and comorbidity | 0.588 (0.586, 0.591) | <.001 |
Age, sex, comorbidity, and CHESS scale | 0.607 (0.605, 0.609) | <.001 | |
Age, sex, comorbidity, and modified frailty index | 0.599 (0.597, 0.601) | 0.005 | |
Age, sex, comorbidity, and full frailty index | 0.600 (0.597, 0.602) | Reference | |
Hospitalization with ALC staya | Age, sex, and comorbidity | 0.578 (0.574, 0.581) | <.001 |
Age, sex, comorbidity, and CHESS scale | 0.602 (0.599, 0.606) | 0.999 | |
Age, sex, comorbidity, and modified frailty index | 0.600 (0.596, 0.603) | 0.002 | |
Age, sex, comorbidity, and full frailty index | 0.602 (0.599, 0.606) | Reference |
Discussion
Among older long-stay home care clients in Ontario, the estimated prevalence of frailty was dependent on the approach taken. When using the full FI, modified FI, and CHESS scale, 19.5, 24.4, and 44.1 % were categorized as frail, respectively. The variation in prevalence estimates with measures was not unexpected. The two FI measures showed substantial agreement with each other [38] but also differ in the frailty domains assessed, with items reflecting social and cognitive deficits not included in the modified FI. The two FI measures captured a different subgroup of home care clients than the CHESS scale, which categorized approximately twice as many clients as frail and demonstrated relatively poor agreement [38] with both FI measures. The CHESS scale is derived based on a consideration of 9 RAI items and is primarily reflective of an acute change in health status (e.g., vomiting, dyspnea, decreased food/fluid intake, change is functional status). It was initially validated in an institutionalized sample where it was observed to be significantly associated with mortality over a 3 year period [25]. These differences may underlie the better performance of CHESS in predicting hospitalization (though none of the frailty measures performed very well for this outcome) and the full FI in predicting institutionalization.
The distribution of continuous FI scores (see Additional file 1: Figure S1) show that it is possible to detect a gradient of frailty within an already generally vulnerable population, providing support for the utility of a FI in this population. Such variability suggests it may be possible to target care to frail and pre-frail individuals [9, 10, 39, 40], though further work is needed to assess whether interventions to prevent, slow or reverse frailty in community-dwelling older adults [39, 41] actually lead to significant health benefits for older clients.
The various health outcomes examined were common in our older home care cohort. All three frailty measures were associated with a significantly increased risk of death, LTC admission, hospitalization, and hospitalization with ALC stay, independent of age, sex, and comorbidity. Although not directly comparable, the risk ratios suggest relatively stronger associations for LTC admission and death compared with the hospitalization endpoints. However, the incorporation of frailty into these models resulted in only modest improvements in predictive validity. While there were statistically significant differences between frailty measures in their ability to predict certain outcomes, the observed AUC differences did not appear clinically meaningful with the possible exception of the enhanced ability of the full FI in predicting LTC admission. As noted above, the full FI contains more items relevant to risk of institutionalization, which might explain why it outperformed the modified FI and the CHESS scale for this outcome. If the calculation is automated and based on previously collected clinical assessment data (e.g., the RAI-HC), the additional items in the full FI would not detract from its feasibility in this setting.
Our findings of an increased risk for poor health outcomes among frail older home care clients are consistent with prior studies in other vulnerable populations [13, 22, 24, 26]. This would include the observation of relatively stronger associations for LTC admission and death than hospitalization [22]. Our study expands on this previous work by showing an increased risk of hospitalization with an ALC stay among frail long-stay home care clients. In Canada, the predominant discharge destination following an ALC hospitalization is a LTC facility [42]. In light of the strong association with LTC admissions, it is not surprising that the frailty measures showed relatively stronger associations for this hospitalization outcome.
A limitation noted for many of the previously published risk prediction models for hospitalization among older adults has been their failure to incorporate measures of patients’ functional status [43, 44]. Our findings suggest that the addition of functional items, which one could argue are well captured by the frailty measures examined here, may offer little predictive gain for this outcome. Hospitalization risk may be influenced more by factors such as advance care planning (where preferences of clients and their family are elicited and documented), the availability of primary care and alternatives to hospitalization, and patterns of previous health care utilization.
The roughly equivalent prevalence of frailty among male and female clients is at variance with findings from studies based on general community samples where higher rates have been reported among women [12, 15, 16]. However, findings regarding sex differences have been far less consistent among more impaired populations, also varying with the frailty measure employed [45, 46]. Compared with women, men receiving formal home care services exhibit relatively higher levels of need (e.g., greater cognitive and physical impairment) [6]. Further supporting this observation, Armstrong et al. reported that the frailest in their home care sample were more likely to be men than women [24].
We also observed a significant association between increasing frailty levels and an increase in the average hours of client support by unpaid caregivers and in the likelihood for caregivers reporting distress. These associations highlight the potential clinical utility of frailty measures in older home care clients. The possible moderating effects of caregiver (or other psychosocial) factors on associations between frailty and adverse health outcomes is an area in need of further research [40].
The breadth and scope of the linked databases examined and the comparative analyses across different frailty measures and health outcomes are important strengths of our study. Some limitations should be noted. First, we derived our measures of frailty using assessment items from the RAI-HC at baseline and then followed home care clients forward for one year to examine health outcomes. During follow-up, clients may have improved or accrued additional health deficits and, therefore, may have been less or more frail at the time of outcome assessment. Second, we limited our analyses to frailty measures derived from existing RAI-HC data. We were not able to evaluate other commonly employed frailty definitions (e.g., the Cardiovascular Health Study physical phenotype [12]) in our comparative analyses. Finally, while the RAI-HC is completed by trained professionals using the best available information (e.g., case discussions with physicians and other providers, health record review) and there is support for its reliability and validity overall [31], selected items may be more vulnerable to possible misclassification bias [47, 48] than others.
Conclusions
The full FI, modified FI, and the CHESS scale led to different estimates of the prevalence of frailty among long-stay home care clients in Ontario. At the same time, all frailty measures were able to discriminate between clients at lower and higher risk for outcomes such as death and institutionalization. Of the three approaches examined, the full FI most accurately predicted LTC admission while the CHESS scale was better at predicting hospitalization though none of the measures performed well for this outcome. We showed that it is feasible to calculate a comprehensive FI as a derived variable in a population-based home care sample using routinely collected data. This has potential to facilitate research on frailty within this sector and foster greater consideration of the impact of frailty on health care resource planning and evaluation.
Important areas for further work include an examination of the sensitivity to change of different frailty measures and their role in predicting and/or modifying the likelihood of other health outcomes relevant to older home care clients (e.g., falls, functional decline, and drug related adverse events) [49]. Finally, there is an urgent need to develop and evaluate interventions for frailty in this vulnerable population.
Abbreviations
ADGs, adjusted diagnosis groups; ALC, alternate level of care; AUC, area under the receiver operating characteristic curve; CHESS, changes in health, end-stage disease and signs and symptoms; ED, Emergency Department; FI, frailty index; LTC, long-term care; RAI, resident assessment instrument; RAI-HC, resident assessment instrument – home care
Funding
Funding for this project was made available through a Canadian Institutes of Health Research (CIHR) grant (# DRB-134053). This study was conducted at the Institute for Clinical Evaluative Sciences (ICES), which is funded by an annual grant from the Ontario Ministry of Health and Long-Term Care (MOHLTC). The opinions, results and conclusions reported in this paper are those of the authors and are independent from the funding sources. No endorsement by ICES or the Ontario MOHLTC is intended or should be inferred. Parts of this material are based on data and information compiled and provided by the Canadian Institute for Health Information (CIHI). However, the analyses, conclusions, opinions and statements expressed herein are those of the authors, and not necessarily those of CIHI. We thank IMS Brogan Inc. for use of their Drug Information Database.
The sponsor did not participate in the design and conduct of the study; collection, management, analysis and interpretation of the data; preparation, review or approval of the manuscript; or the decision to submit the manuscript for publication.
Availability of data and materials
The individual-level data underlying this study are based on records generated from the administration of Ontario’s publicly funded health system. The Institute of Clinical Evaluative Sciences (ICES) has a special designation under Ontario’s Personal Health Information Protection Act to use this data in studies that evaluate health care delivery and outcomes. This designation is granted by the Information and Privacy Commissioner of Ontario, and is contingent on a triennial review and ongoing oversight of the privacy practices at ICES. A variety of measures are deployed to protect the personal health information entrusted to ICES and, under the Personal Health Information Protection Act (Ontario Regulation 329/04), the underlying data are legally not allowed for public repository.
Authors’ contributions
CJM: study conception, design and funding, data access and interpretation, contributed to initial draft and involved in all critical revisions of the manuscript. MAC: data access, analysis and interpretation, responsible for first draft and contributed to critical revisions of the manuscript. CD: data access, analysis and interpretation and contributed to critical revisions of the manuscript. DBH: study conception and design, data interpretation and involved in all critical revisions of the manuscript. SEB: study conception, design and funding, data access and interpretation and contributed to critical revisions of the manuscript. JEA, SG, DS, KT and WPW: study conception and design, data interpretation and contributed to critical revisions of the manuscript. All authors have read and approved the final version of the manuscript.
Competing interests
The authors declare that they have no competing interests.
Consent for publication
Not applicable.
Ethics approval and consent to participate
Ethics approval was obtained from the University of Waterloo Research Ethics Committee (ORE File #:19950) and the Research Ethics Board of Sunnybrook Health Sciences Centre, Toronto, Ontario, Canada.
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