Abstract
Objective
Depressive symptoms are known modifiable factors of cognitive impairment in older adults. However, the pathway through which depressive symptoms lead to cognitive impairment is not well understood. This study aimed to investigate whether homebound status (defined as usually unable to leave home unassisted) mediates the association between depressive symptoms and cognitive impairment in community-dwelling older adults in the USA.
Design
A secondary analysis of cross-sectional data.
Setting(s)
Communities in the USA.
Participants
Community-dwelling older adults (N=7537) from the 2011 National Health and Aging Trends Study, a nationally representative survey of Medicare Beneficiaries in the USA.
Main outcome measures
Participants’ cognitive impairment status was classified using a composite measure. Depressive symptoms were assessed using Patient Health Questionnaire-2. Homebound status was determined by the frequency, difficulty and needing help in getting outdoors. We used logistic regression and the Paramed command in STATA to analyse whether homebound mediated the association between depressive symptoms and cognitive impairment.
Results
Participants were on average, 77.7 years old, female (58.3%) and non-Hispanic white (68.1%). About 26% of the participants were classified as having cognitive impairment, 16% reported depressive symptoms and 25% were homebound. Depressive symptoms (adjusted OR, 1.60; 95% CI 1.36 to 1.89) and homebound status (adjusted OR, 1.58; 95% CI 1.34 to 1.86) were independently associated with cognitive impairment. Homebound significantly mediated 12.5% of the total effect between depressive symptoms and cognitive impairment, with significant indirect effect (OR, 1.07; 95% CI 1.04 to 1.10), direct effect (OR, 1.61; 95% CI 1.36 to 1.91) and total effect (OR, 1.72; 95% CI 1.46 to 2.03).
Conclusions
This study supports a mediating role of homebound status in the relationship between depressive symptoms and cognitive impairment. Interventions to promote outdoor mobility should be studied for their ability to delay cognitive impairment for older adults with depressive symptoms.
Keywords: EPIDEMIOLOGY, GERIATRIC MEDICINE, MENTAL HEALTH, Dementia, Depression & mood disorders
STRENGTHS AND LIMITATIONS OF THIS STUDY.
The strengths of this study include the use of nationally large sample data and adjustment for potential confounders including demographics and health-related factors.
The cross-sectional design does not examine causality.
All indicators were self-reported retrospectively which may cause recall bias and report errors.
The measurement of homebound did not collect reasons why individuals did not leave their homes.
Introduction
Cognitive impairment (including mild cognitive impairment and dementia1) causes disabilities in older adults’ physical and psychological functions and is a major public health concern.2 3 Approximately 25% of US adults aged 50 and over suffer from cognitive impairment and this rate increases with age,1 bringing a huge economic burden to families and society.4 Older adults with cognitive impairments have a high and growing demand for long-term care, which poses a significant challenge for healthcare systems, healthcare providers and families. Thus, it is imperative to identify the modifiable factors and develop effective strategies to prevent and slow the progression of cognitive impairment in older adults.
Depressive symptoms are common in older adults and are associated with physical disability,5 social isolation6 and cardiovascular diseases,7 all of which have been identified as contributors to declines in cognition.8 9 A systematic review concluded that depressive symptoms are an independent risk factor for dementia.10 In addition, multiple systematic reviews found that depressive symptoms are associated with the progression of mild cognitive impairment to dementia.11–13 Despite these well-established associations between depressive symptoms and cognitive impairment, the mediating mechanisms of the association remain unclear.
In this paper, we examined homebound status as a potential mediator between depressive symptoms and cognitive impairment. Being homebound, defined as limited at home, is closely related to depression and cognitive impairment. Homebound older adults have consistently been found to experience depression in high numbers; in one population-based study, 59% of older adults who had not left their homes in the previous month had positive depressive symptoms.14–17 Prior research has also found cognitive impairment more prevalent in the homebound population than the non-homebound population.18 19 The confluence of mental health, physical and social impairments that result in homebound status,20 may lead to cognitive impairment and should be better understood as a potential target of intervention. For example, previous studies have shown that older adults with depressive symptoms were more likely to have physical impairments and loss of interest or energy in social participation,5 21 resulting in homebound status.19 20 Rates of physical activity and social participation, well-known protective factors against cognitive impairment,22 are low in homebound older adults and may contribute to the higher rates of cognitive impairment in this population.20
Fortunately, homebound status is modifiable and can be improved using assistive devices, modifying the home environment and accessing transportation.15 It is therefore important to investigate the potential of homebound status as a target of interventions to improve cognitive function. However, to the best of our knowledge, no study has attempted to investigate whether homebound status mediates the association between depressive symptoms and cognitive impairment, suggesting the pathway through homebound status remains unclear. Given the reversibility of homebound status and depressive symptoms and the heavy burden of cognitive impairment, it is also important to understand the mediating role of homebound status between cognitive impairment and depressive symptoms. The study was to examine whether homebound status mediates the association between depressive symptoms and cognitive impairment in a nationally representative sample of community-dwelling older adults in the USA. We hypothesised that homebound status is a significant mediator between depressive symptoms and cognitive impairment in community-dwelling older adults.
Methods
Design and sample
We used the first round (2011) of data from the National Health and Aging Trends Study (NHATS),23 a nationally representative longitudinal cohort study of older adults in the USA who are Medicare beneficiaries aged 65 and older.24 The NHATS study began in 2011 and aimed to understand the disability trends of older adults in late life. In the current study, data obtained from older adults who were aged 65 or above and lived in the community were included in data analyses. In the initial round, a total of 7609 participants who lived in the community completed the sample person interview. We excluded 72 participants who had incomplete data on depressive symptoms, homebound or cognitive function, for a resulting analysis sample size of 7537. Excluded participants were older, living alone, with less education, were less likely to perform vigorous activities, had a stroke, and tended to have more activities of daily living (ADL) impairments, visual impairment and auditory impairment, compared with those who were not excluded. The NHATS used downloadable, non-identifiable and publicly available data25 The current analyses were deemed exempt from review by the Xiangya School of Nursing Ethic Committee of Central South University.
Measurement
Dependent variables
Cognitive function was determined by a previously modified NHATS dementia definition including a diagnosis from physicians (self-reported), assessment of cognitive function in three domains (memory, orientation and executive function) and AD8 Dementia Screening Interview provided by proxy respondents.26 The AD8 contained eight items and ranged 0–8. Cognitive impairments were determined by a cut-off of 2 and higher. The Cronbach’s α coefficient of AD8 was 0.84.27 Participants were classified into three groups as follows probable dementia, possible dementia and no dementia. Probable dementia was assessed by (1) a diagnosis of dementia; (2) the AD8 scores ≥2 or (3) scores ≤1.5. SD below the mean in at least 2 of 3 cognitive performance tests; possible dementia was determined by a score of ≤1.5 SDs below the mean in 1 cognitive performance test. All other participants were classified as having no dementia. We considered participants with a classification of probable dementia or possible dementia as having cognitive impairment; we considered participants with a classification of no dementia as without cognitive impairment. The NHATS dementia definition (defined as probable or possible dementia) has shown high sensitivity (85.7%) and specificity (83.7%) compared with a structured in-home clinical measurement in the landmark Aging, Demographics and Memory Study.26 For terminology consistent with the cognitive impairment instrument, the term ‘cognitive impairment’ was used throughout this article to replace dementia.
Independent variable
Depressive symptoms were measured using the Patient Health Questionnaire-2 (PHQ-2), a well-validated screening instrument for depression status.28 Participants were asked: ‘Over the last month, how often have you: 1) had little interest or pleasure in doing things; 2) felt down, depressed, or hopeless’. Responses were recorded on a 4-point Likert scale (scored 0–3) with total scores ranging from 0 to 6. A higher score suggested more depressive symptoms. Following the recommendation from previous studies, we used a cut-off of 3 and higher to determine depressive symptoms. The PHQ-2 had a good criterion validity for major depression.29 The cut-off of 3 has a sensitivity of 0.79, a specificity of 0.86 and the area under the curve of 0.90 for any type of depressive disorder.28
Mediator
Based on the measurement developed by Ornstein and colleagues, homebound status was measured using four questions based on the reported frequency of outdoor mobility.15 First, participants were asked about the frequency of going outside, and response options were on a 5-point Likert scale: never; rarely (≤1 day per week); some days (2–4 days per week); most days (5–6 days per week) and every day. Participants reporting going outside at least 2 days per week were asked whether they needed help from others to go outside. Those who reported needing help were also asked about the frequency of going outside independently. Those who reported ever going outside by themselves were asked whether they had any difficulties leaving home independently. Participants were classified as homebound if they never left home, or left home with any difficulties and assistance. All other participants were classified as non-homebound.15
Covariates
Demographic and health-related characteristics that are common risk factors for depression, homebound status and cognitive impairment were included as covariates in analyses.
Demographic characteristics included age,1 sex (male/female),30 race/ethnicity (non-Hispanic white, non-Hispanic black, Hispanic and other),31 education (less than high school, high school, college or vocational school and bachelor or higher)32 and living arrangement (alone, with spouse/partner only, with others only, with spouse/partner and with others).33
Health-related characteristics included smoking status (never smoker and current/former smoker)8; whether they performed vigorous activities last month (yes/no)34; body mass index (BMI) (normal/obesity (≥30 kg/m2))8; visual impairment (yes/no)35; auditory impairment (yes/no)36; diagnoses of hypertension (yes/no),8 diabetes (yes/no)8 and stroke (yes/no)37; number of ADL impairments38; whether the subjects were hospitalised in the last 12 months (yes/no).39
Statistical analysis
Demographic and health-related characteristics were described using frequencies, proportions, means and SDs. χ2 test and two sample t-test were used to test the differences between groups with and without cognitive impairment for categorical and continuous variables, respectively. Using Baron and Kenny’s method for mediation,40 we assessed the associations among depressive symptoms, homebound status and cognitive impairment in four logistic regression models. The first model assessed the direct relationship between the independent variable depressive symptoms and the dependent variable cognitive impairment. The second model examined whether depressive symptoms were associated with the hypothesised mediator homebound status. The third model evaluated the association between the hypothesised mediator homebound status and cognitive impairment. The fourth model estimated the association between the independent variable depressive symptoms and the dependent variable cognitive impairment on inclusion of the hypothesised mediator homebound status to the model. All models were adjusted for demographics and health-related factors.
Because all the associations in the above models were significant, we were able to further test homebound status as a mediator following Baron and Kenny’s approach and using the Paramed command in Stata.40 This procedure estimates the natural direct effects, natural indirect effects and marginal total effects in the presence of exposure–mediator interaction. The product of direct and indirect effects was expressed as the total effect. We estimated direct and indirect effects using logistic regression models and performed a bootstrapping analysis with 1000 replications both with and without adjusting for covariates. The proportion of effect mediated by homebound status was calculated as the log of the indirect effect divided by the log of the total effect.
Sensitivity analyses were performed to test the robustness of the findings. We excluded any data provided by proxy respondents (n=583) and reran the analysis (see online supplemental tables 1–3). ORs and 95% CI were reported. Missing values on covariates ranged from 0.1% (stroke) to 3.5% (BMI). Given the large sample size, no particular technique was used to handle missing data. P values less than 0.05 indicated statistical significance. All analyses were performed in Stata/SE V.15.0 (Stata Corp).
bmjopen-2022-065536supp001.pdf (147.1KB, pdf)
Patient and public involvement
No patients were involved in the development of the question, design or data interpretation.
Results
Characteristics of all participants and their comparisons by cognitive status are presented in table 1 (N=7537). The mean age of the participants was 77.7 years old. Fifty-eight per cent were female and 68% were non-Hispanic white. About 26% of the participants had cognitive impairment, 16% reported depressive symptoms and 25% were homebound. Compared with participants with no cognitive impairment, those with cognitive impairment were more likely to be older and less educated, have ADL, visual and auditory impairments, have comorbidities of diabetes and stroke, and have been hospitalised (p<0.001 for all comparisons). The prevalence of depressive symptoms and homebound status were significantly higher for those with cognitive impairment than those without (27.4% vs 12.0% for depression status and 48.1% vs 16.7% for homebound).
Table 1.
Characteristics of community-dwelling older adults, stratified by cognitive impairment status
| Characteristics | Total (N=7270–7537)* | Cognitive impairment (n=1849–1988) | No cognitive impairment (n=5421–5549) | P value |
| Age, M±SD | 77.7±7.9 | 81.8±7.8 | 76.2±7.3 | <0.001 |
| Sex, n (%) | 0.800 | |||
| Female | 4397 (58.3) | 1155 (58.1) | 3242 (58.4) | |
| Male | 3140 (41.7) | 833 (41.9) | 2307 (41.6) | |
| Race/ethnicity, n (%) | <0.001 | |||
| White, non-Hispanic | 5137 (68.1) | 1119 (56.3) | 4018 (72.4) | |
| Black, non-Hispanic | 1648 (21.9) | 563 (28.3) | 1085 (19.5) | |
| Hispanic | 449 (6.0) | 191 (9.6) | 258 (4.7) | |
| Other | 303 (4.0) | 115 (5.8) | 188 (3.4) | |
| Education, n (%) | <0.001 | |||
| Less than high school | 2020 (27.1) | 906 (46.6) | 1114 (20.3) | |
| High school | 2056 (27.6) | 492 (25.3) | 1564 (28.4) | |
| Some college or vocational school | 1801 (24.2) | 307 (15.8) | 1494 (27.1) | |
| College or higher | 1570 (21.1) | 240 (12.3) | 1330 (24.2) | |
| Living arrangement, n (%) | <0.001 | |||
| Alone | 2435 (32.4) | 680 (34.3) | 1755 (31.7) | |
| With spouse/partner only | 3036 (40.5) | 538 (27.2) | 2498 (45.2) | |
| With others only | 1351 (18.0) | 568 (28.7) | 783 (14.2) | |
| With spouse/partner and with others | 684 (9.1) | 195 (9.8) | 489 (8.9) | |
| Smoking status, n (%) | <0.001 | |||
| No | 3721 (49.4) | 1064 (53.7) | 2657 (47.9) | |
| Yes | 3807 (50.6) | 919 (46.3) | 2888 (52.1) | |
| Vigorous activity, n (%) | <0.001 | |||
| No | 4970 (66.0) | 1652 (83.2) | 3318 (59.8) | |
| Yes | 2563 (34.0) | 333 (16.8) | 2230 (40.2) | |
| BMI, n (%) | <0.001 | |||
| Normal (<30 kg/m2) | 5316 (72.1) | 1479 (80.0) | 3837 (70.8) | |
| Obesity (≥30 kg/m2) | 1954 (28.9) | 370 (20.0) | 1584 (29.2) | |
| Visual impairment, n (%) | <0.001 | |||
| No | 6684 (89.1) | 1540 (78.2) | 5144 (93.0) | |
| Yes | 819 (10.9) | 429 (21.8) | 390 (7.0) | |
| Auditory impairment, n (%) | <0.001 | |||
| No | 5716 (75.8) | 1356 (67.7) | 4371 (78.8) | |
| Yes | 1821 (24.2) | 643 (32.3) | 1178 (21.2) | |
| Hypertension, n (%) | 0.367 | |||
| No | 2467 (32.8) | 634 (32.0) | 1833 (33.1) | |
| Yes | 5061 (67.2) | 1350 (68.0) | 3711 (66.9) | |
| Diabetes, n (%) | <0.001 | |||
| No | 5631 (74.7) | 1407 (70.9) | 4224 (76.1) | |
| Yes | 1903 (25.3) | 578 (29.1) | 1325 (23.9) | |
| Stroke, n (%) | <0.001 | |||
| No | 6655 (88.4) | 1613 (81.2) | 5042 (90.9) | |
| Yes | 876 (11.5) | 373 (18.8) | 503 (9.1) | |
| Number of ADL impairments, M±SD | 1.3±0.9 | 1.8±1.1 | 1.2±0.6 | <0.001 |
| Hospitalisation, n (%) | <0.001 | |||
| No | 5770 (76.6) | 1350 (68.0) | 4420 (79.7) | |
| Yes | 1759 (23.4) | 634 (32.0) | 1125 (20.3) | |
| Depressive symptoms, n (%) | <0.001 | |||
| No | 6328 (83.0) | 1444 (72.6) | 4884 (88.0) | |
| Yes | 1209 (16.0) | 544 (27.4) | 665 (12.0) | |
| Homebound, n (%) | <0.001 | |||
| No | 5652 (75.0) | 1032 (51.9) | 4620 (83.3) | |
| Yes | 1885 (25.0) | 956 (48.1) | 929 (16.7) |
*Sample size has a range because missing values on covariates ranged from 0.1% (stroke) to 3.5% (BMI). Given the large sample size, no particular technique was used to handle missing data.
ADL, activities of daily living; BMI, body mass index; M, mean.
Table 2 presents the results of the associations among cognitive impairment, depressive symptoms and homebound status in accordance with the Baron and Kenny approach to study mediation. After adjusting for demographics and health-related factors, compared with participants without depressive symptoms or homebound status, those with depressive symptoms (adjusted OR, 1.67; 95% CI 1.42 to 1.97) or homebound status (adjusted OR, 1.65; 95% CI 1.40 to 1.94) had higher odds of cognitive impairment. Depressive symptoms were also a significant risk factor for homebound status (adjusted OR, 2.00; 95% CI 1.67 to 2.40). Additionally, both homebound status (adjusted OR, 1.58; 95% CI 1.34 to 1.86) and depressive symptoms (adjusted OR, 1.60; 95% CI 1.36 to 1.89) were statistically significantly associated with cognitive impairment when they were both included as independent variables in the same model.
Table 2.
Results of logistic regression analyses of associations among depressive symptoms, homebound status and cognitive impairment
| Independent variable(s) | Effect size for association, OR (95% CI)* | |||
| Dependent variable | ||||
| Model 1: cognitive impairment | Model 2: homebound status | Model 3: cognitive impairment | Model 4: cognitive impairment | |
| Depressive symptoms | 1.67 (1.42 to 1.97)*** | 2.00 (1.67 to 2.40)*** | NA | 1.60 (1.32 to 1.89)*** |
| Homebound status | NA | NA | 1.65 (1.40 to 1.94)*** | 1.58 (1.34 to 1.86)*** |
*p<0.05, **p<0.01, ***p<0.001.
*All models adjusted for demographics (age, sex, education, race/ethnicity, living arrangement) and health-related characteristics (smoke, body mass index, vigorous activity, visual impairment, auditory impairment, hypertension, diabetes, stroke, number of activities of daily living impairments, hospitalisation).
NA, not applicable.
Table 3 and figure 1 show the indirect contribution of being homebound in the relationship between depressive symptoms and cognitive impairment. Homebound status statistically significantly mediated this relationship. It partially explained the relationship; the contribution of being homebound was 40.4% of the association between depressive symptoms and cognitive impairment in the unadjusted model (model 1), and this proportion decreased to 12.5% after adjusting for all covariates (model 3).
Table 3.
Mediation of homebound status in the association between depressive symptoms and cognitive impairment
| Model 1* OR (95% CI) | Model 2† OR (95% CI) | Model 3‡ OR (95% CI) | |
| Natural direct effect | 1.93 (1.68 to 2.22)*** | 1.88 (1.61 to 2.18)*** | 1.61 (1.36 to 1.91)*** |
| Natural indirect effect | 1.56 (1.48 to 1.64)*** | 1.33 (1.27 to 1.39)*** | 1.07 (1.04 to 1.10)*** |
| Marginal total effect | 3.01 (2.61 to 3.46)*** | 2.49 (2.15 to 2.90)*** | 1.72 (1.46 to 2.03)*** |
| Proportion mediated§ | 40.4% | 31.3% | 12.5% |
*Model 1: independent variables of interest.
†Model 2: model 1+demographic covariates (age, sex, education, race/ethnicity, living arrangement).
‡Model 3: model 2+health-related covariates (smoke, body mass index, vigorous activity, visual impairment, auditory impairment, hypertension, diabetes, stroke, number of activities of daily living impairments, hospitalisation).
§Proportion meditated by homebound status was calculated as the log of the indirect effect divided by the log of the total effect.
Figure 1.
Mediation model of homebound status between depressive symptoms and cognitive impairment. The figure depicts that homebound status significantly mediated the relationship between depressive symptoms and cognitive impairment (NIE, aOR; 95% CI 1.04 to 1.10), with significant direct effect of depressive symptoms (NDE, aOR=1.61; 95% CI 1.36 to 1.91) and significant total effect (aOR=1.72; 95% CI 1.46 to 2.03) after adjusting for all covariates. aOR, adjusted OR; NDE, natural direct effect; NIE, natural indirect effect.
Results from a sensitivity analysis suggested that homebound status statistically significantly mediated the association between depressive symptoms and cognitive impairment (adjusted OR, 1.05; 95% CI 1.02 to 1.08), even after excluding data from proxy respondents (online supplemental table 3, additional information see online supplemental tables 1 and 2).
Discussion
We examined the mediating role of homebound status in the association of depressive symptoms and cognitive impairment using a nationally representative sample of community-dwelling older Americans. Our study found that depressive symptoms and homebound status were independently associated with cognitive impairment. Moreover, more than 10% of the effect of depressive symptoms on cognitive impairment was mediated by homebound status, suggesting that one of the ways the depression status influences cognitive impairment is through the decreased mobility outside the home that defines homebound status. Our findings shed light on homebound status as a target of intervention to prevent and slow cognitive impairment in later life.
Our results showed that depressive symptoms and homebound status were each independently associated with a greater risk of cognitive impairment; findings are supported by previous studies.13 18 Depression is a well-established predictor of cognitive impairment; however, we found a similar magnitude of association between homebound status and cognitive impairment as between depression symptoms and cognitive impairment, after accounting for demographic and health-related factors. This result was inconsistent with a cross-sectional study by Meng et al which suggested that cognitive impairment was more strongly associated with homebound status compared with depressive symptoms.41 Possible explanations for different results are differences in the homebound status measures, covariates, and the US and Chinese cultures. Meng et al’s study included older adults from a rural province in China, with a smaller sample size (N=720) and adjusted for sociodemographic variables only.41
The mediation findings of this study may be explained through several potential mechanisms. Depressed older adults often experience loss of interest and social connection,22 and have no energy to participate in outside activities, which for some leads to reduced mobility and becoming homebound.15 19 42 There is robust evidence that physical activity and social participation are effective strategies to prevent cognitive impairment,22 and that homebound older adults are less likely to benefit from these strategies. Homebound status may also mediate the effects of depression on cognitive impairment via other mechanisms such as nutrition disorders, social isolation and hospitalisation,19 43 all of which have been associated with both depression and homebound status. The results of two previous studies (one cross-sectional44 and one prospective45) found that functional disability mediated the relationship between depression status and cognitive impairment, and offer additional support to our mediation findings. Although homebound status is not equivalent to functional disability, there are overlapping characteristics between homebound older adults and those with a functional disability; older adults with functional disability frequently report difficulty going outside regularly and are at increased risk of being homebound.46
This study has important implications for public health practice and research. Our findings suggest the usage of efforts to improve cognitive function by reducing the effect of depressive symptoms and homebound status. For example, interventions that support depressed older adults to maintain ideal outdoor mobility through health education, psychosocial interventions, and creating a safe and convenient environment, may serve to decrease the risk of cognitive impairment. Some interventions have shown their potential to reduce depressive symptoms and improve cognitive impairments in depressed older adults, such as physical exercise.21 47 48 Yet, existing interventions are geared toward improving other outcomes of home-dwelling older adults, instead of improving the status of the homebound. Some evidence-based physical activity intervention programmes, such as Community Aging in Place-Advancing Better Living for Elders and Lifestyle Interventions and Independence for Elders, have shown the effect to increase life-space mobility, falls efficacy and reduce cognitive frailty among community-dwelling older adults.49 50 Future research should further identify these programmes’ effects on changing homebound status. The Centers for Medicare & Medicaid Services have suggested improving health services for homebound older adults who receive healthcare at home.51 We did not find studies of mobility interventions to reduce cognitive impairment among homebound older adults and suggest this as an area of future inquiry. By recognising the associations of depressive symptoms and homebound with cognitive impairment, healthcare professionals can screen people who are at high risk of cognitive impairment or have cognitive impairment more easily by examining their depressive symptoms and homebound status profiles in their routine practice. Last but not least, for older adults with depressive symptoms or who are homebound, healthcare professionals can focus on whether these older adults have additional risk factors for cognitive impairment, such as physical inactivity, obesity and social isolation, all of which are common in depressed or homebound older adults. Proactively managing these modifiable risk factors is beneficial to delay the onset of cognitive impairment and diagnosing it early.
To the best of our knowledge, this study is the first to explore the mediation role of homebound status in the relationship between depressive symptoms and cognitive impairments in older adults. The strengths of this study include the use of nationally large sample data and adjustment for potential confounders including demographics and health-related factors. However, several limitations of the study should be noted. First, the cross-sectional design does not examine causality, suggesting future studies can further assess causal relationships among depressive symptoms, homebound status and cognitive impairments using a prospective research design. Second, all indicators were self-reported retrospectively which may cause recall bias and report errors. Particularly, when we assessed homebound status, a month recall time may be too long for participants or their proxies to recall accurately. Third, Medicare defined a homebound individual as requiring ‘taxing effort’ (ie, physical, or personal assistance) to leave their home,52 which was consistent with the NHATS homebound definition. However, the measurement of homebound was limited by the items and skip patterns within the NHATS Mobility Questionnaire. For example, the mobility questions did not collect reasons why individuals did not leave their homes.15
Conclusion
Based on a nationally representative sample of older adults in the USA, we found that depressive symptoms and homebound status were associated with cognitive impairment, and homebound status partially mediated the relationship between depressive symptoms and cognitive impairment. Therefore, for future public health efforts on preventing cognitive impairment in depressed older adults, homebound status should be taken into account.
Supplementary Material
Footnotes
Contributors: WP: concept and design, analysis, drafting of the initial manuscript and revision. CEM: critical feedback and revision of the manuscript. SMO: critical feedback and revision of the manuscript. WW: critical feedback and revision of the manuscript. YL: revision of the manuscript. CM: revision of the manuscript. ML: supervision, validation, interpretation of data and critical revision of the manuscript. ML is the guarantor.
Funding: The publication of this manuscript was supported by the Youth Grant from the National Natural Science Foundation of China (Grant No. 72004237) and the Youth Grant from National Natural Science Foundation of Hunan Province, China (Grant No.2021JJ40798).
Competing interests: None declared.
Patient and public involvement: Patients and/or the public were not involved in the design, or conduct, or reporting, or dissemination plans of this research.
Provenance and peer review: Not commissioned; externally peer reviewed.
Supplemental material: This content has been supplied by the author(s). It has not been vetted by BMJ Publishing Group Limited (BMJ) and may not have been peer-reviewed. Any opinions or recommendations discussed are solely those of the author(s) and are not endorsed by BMJ. BMJ disclaims all liability and responsibility arising from any reliance placed on the content. Where the content includes any translated material, BMJ does not warrant the accuracy and reliability of the translations (including but not limited to local regulations, clinical guidelines, terminology, drug names and drug dosages), and is not responsible for any error and/or omissions arising from translation and adaptation or otherwise.
Data availability statement
Data are available in a public, open access repository. Data are available in a public, open access repository. The NHATS data analysed in the current study are available for research purposes at www.nhats.org.
Ethics statements
Patient consent for publication
Not applicable.
Ethics approval
This study involves human participants and was approved by the Johns Hopkins Bloomberg School of Public Health Institutional Review Board (JHSPH IRB # 00002083). Participants gave informed consent to participate in the study before taking part.
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Associated Data
This section collects any data citations, data availability statements, or supplementary materials included in this article.
Supplementary Materials
bmjopen-2022-065536supp001.pdf (147.1KB, pdf)
Data Availability Statement
Data are available in a public, open access repository. Data are available in a public, open access repository. The NHATS data analysed in the current study are available for research purposes at www.nhats.org.