Volume 2025, Issue 1 1593646
Research Article
Open Access

The Impact of Community-Level Social and Economic Factors on Healthcare Access Among Individuals With Mental Illness

Jonathan Phillips

Corresponding Author

Jonathan Phillips

Department of Social Work , University of Minnesota Duluth , Duluth , Minnesota, USA , umn.edu

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Amy Blank Wilson

Amy Blank Wilson

School of Social Work , University of North Carolina at Chapel Hill , Chapel Hill , North Carolina, USA , unc.edu

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Todd Jensen

Todd Jensen

School of Education , University of North Carolina at Chapel Hill , Chapel Hill , North Carolina, USA , unc.edu

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Steven C. Marcus

Steven C. Marcus

School of Social Policy & Practice , University of Pennsylvania , Philadelphia , Pennsylvania, USA , upenn.edu

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David Ansong

David Ansong

School of Social Work , University of North Carolina at Chapel Hill , Chapel Hill , North Carolina, USA , unc.edu

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Rainier Masa

Rainier Masa

School of Social Work , University of North Carolina at Chapel Hill , Chapel Hill , North Carolina, USA , unc.edu

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First published: 11 July 2025
Academic Editor: Sagit Lev

Abstract

Aims: We examined how community-level socioeconomic deprivation and residential stability impact healthcare access among a sample of individuals with mental illness.

Methods: We linked five years of the Medical Expenditure Panel Survey (MEPS; 2013–2017) with community-level data, drawing a sample of adults with mental illness in the United Sates (N = 5444). Descriptive statistics and bivariate and multivariable logistic regression models are presented.

Results: Socioeconomic deprivation was negatively associated with access to a usual source of care and positively associated with delaying or forgoing prescription medication. Residential stability was positively associated with having a usual source of care and negatively associated with forgoing or delaying needed care and prescription medication. Residential stability remained negatively associated with delayed or forgone healthcare in adjusted models.

Conclusion: Community-level factors are important determinants of healthcare access above and beyond individual-level predictors. Efforts to improve healthcare access among individuals with mental illness may be optimized by also targeting broader social and economic contexts.

1. Introduction

People with mental illness (MI) in the United States (U.S.) face a multitude of barriers to accessing both mental and physical healthcare, resulting in the suboptimal receipt of care and contributing to disparities in health and healthcare outcomes [14]. Facilitating access to healthcare is therefore a critical component of improving health and healthcare outcomes for this population. Commonly cited barriers to accessing healthcare among people with MI include impaired cognition, general distress and disorganization, negative attitudes toward treatment, inadequate transportation, lack of care coordination, and the cost of health services [510].

Barriers to healthcare access significantly impact people with MI. For example, compared to individuals in the general population, individuals with MI are up to 50% less likely to report having a usual source of care (USC), an important enabling factor that has been linked to the adequate and timely receipt of care [1113]. Additionally, individuals with MI are seven times more likely to report difficulty accessing healthcare than individuals in the general population [11]. Ultimately, the inadequate receipt of needed care among individuals with MI can result in increased acute care use, preventable healthcare costs, homelessness, incarceration, diminished quality of life, and suicide [2, 1419].

A number of individual- and system-level approaches have been developed and deployed in response to findings of diminished access to care for individuals with MI (see [1] for a review of barriers to care and related interventions; [2022]). While these efforts have shown promise, they largely benefit individuals who already have an existing connection to healthcare systems and pay little attention to the broader social and economic contexts that impact health and healthcare outcomes for individuals with MI [12, 23, 24]. Therefore, the “upstream” community-level social and economic contexts that prevent individuals from even approaching healthcare systems in the first place are considered a potentially potent, yet understudied, point of intervention [14, 25, 26].

A growing body of literature, emerging from increasingly popular discussions around the social determinants of health (see [27]), is investigating how social and economic aspects of communities impact healthcare access and utilization [12, 2833]. For example, community-level socioeconomic status (SES) has been shown to influence the need for healthcare by influencing health behaviors via the availability of healthy foods and opportunities to exercise [33, 34]. Community-level SES has also been linked to the availability of quality healthcare, with poorer neighborhoods having greater difficulty recruiting and retaining the most qualified providers [12, 23, 35].

Residential stability can help facilitate access to services by strengthening social networks and support systems within communities which, in turn, can influence how individuals evaluate their own health and healthcare needs, affect an individual’s willingness to seek care, and facilitate the sharing of knowledge and resources necessary to initiate care [31, 36, 37]. In this vein, a systematic review by Derose & Vara [38]​ found that trusting and cooperative relationships within a person’s social network were related to overall improvements in healthcare access generally. However, less is known about how these community-level factors impact healthcare outcomes among individuals with MI specifically. In addition, previous research has largely focused on access to, and utilization of, mental health (MH) treatment specifically. There is much to be learned about the factors that impact the ability of individuals with MI to access healthcare services more generally.

The current study helps fill this gap by examining how indicators of community-level SES and residential stability are associated with access to healthcare among a sample of individuals with MI drawn from a nationally representative survey in the U.S. (see Methods section for a description of how we operationalize “access to healthcare”).

2. Methods

2.1. Research Design

Pooled years of the Medical Expenditure Panel Survey (MEPS; Panels 17–21, 2013–2017) were used to establish the study cohort and provided information related to participant’s individual-level healthcare experiences. Each individual in the MEPS is followed for a 2-year period. To address the study aims, community-level data were linked to the individual-level MEPS data. The Area Deprivation Index (ADI; [39]) was used to capture community-level SES and residential stability was captured via U.S. census data. For the current study, and as described in more detail below, all variables except those pertaining to MH conditions were drawn from each respondent’s second year in the MEPS.

2.1.1. Study Sample

The study sample included 5444 individuals who met the following criteria: (1) 18 years of age or older, (2) had a MH condition of schizophrenia or a related disorder, bipolar disorder, depressive disorder, or posttraumatic stress disorder (PTSD) (see Table A1 for ICD codes used to classify MH conditions), and (3) reported being non-Hispanic White (hereafter “White”), non-Hispanic Black (hereafter “Black or African American”), or Hispanic. Individuals falling under the MEPS categories of “non-Hispanic Asian only” and “non-Hispanic Other Race or Multiple Race” were excluded due to small subgroup sizes.

Participant MH conditions were established during each respondent’s first year in the MEPS (i.e., 2012–2016) using the MEPS conditions files. This ensured that individuals in the study sample had an eligible MH diagnosis before outcomes were measured. All other variables were drawn from each respondent’s second year in the MEPS during 2013–2017. It should be noted that the MH condition categories reported in Table 1 were determined hierarchically and in mutually exclusive categories in the order they are listed in both Table 1 and Table A1. These are reported categorically for the sake of transparency and replicability, though the ability to clearly differentiate between diagnoses based on ICD codes (as well as DSM criteria) is both limited and problematic (see [40]).

Table 1. Demographic and clinical characteristics of study sample (N = 5444).
Total (N = 5444)
M (SD)
Age 50.1 (16.4)
Residential stability1 84.4 (8.2)
  
N %
  
Socioeconomic deprivation1
 First quintile (least disadvantaged) 738 (13.6%)
 Second quintile 1100 (20.2%)
 Third quintile 1143 (21.0%)
 Fourth quintile 1215 (22.3%)
 Fifth quintile (most disadvantaged) 1248 (22.9%)
Health fair or poor 1961 (36.0%)
Mental health (MH) fair or poor 1789 (32.9%)
MH diagnosis2
 Schizophrenia 139 (2.6%)
 Bipolar 515 (9.6%)
 Depression 4670 (85.8%)
 PTSD 120 (2.2%)
Race/ethnicity
 White 3314 (60.9%)
 Black or African American 903 (16.6%)
 Hispanic 1227 (22.5%)
Insurance coverage
 Any private coverage 2710 (49.8%)
 Only public coverage 2252 (41.4%)
 Uninsured 482 (8.9%)
Male 1755 (32.2%)
Education
 No diploma/GED 1035 (19.0%)
 H.S. or G.E.D 3264 (60.0%)
 College 1145 (21.0%)
Married 2060 (37.8%)
Employed 2292 (42.1%)
Household income < 125% FPL 1800 (33.1%)
Family size
 1 1629 (29.9%)
 2–3 2613 (48.0%)
 4+ 1202 (22.1%)
Urban residence 4632 (85.1%)
  • 1Community-level independent variable. Residential stability is measured as the percentage of individuals in a census tract who had lived in the same residence 1 year prior. Socioeconomic deprivation is measured using the Area Deprivation Index (ADI).
  • 2Mental health diagnoses are reported categorically for the sake of transparency and replicability. The authors acknowledge that differentiating these diagnoses as “mutually exclusive” based on ICD codes does not capture the complex nature of these mental health conditions.

2.2. Variables

2.2.1. Access to Healthcare

Three study outcomes were used to capture access to healthcare: having to delay or forgo healthcare that the respondent or a doctor believed necessary in the past 12 months (hereafter “delayed or forgone healthcare”); having to delay or forgo prescription medication that the respondent or a doctor believed necessary in the past 12 months (hereafter “delayed or forgone prescription medication”); and having a USC. The MEPS ascertains whether a person has a USC by asking if “there is a particular doctor’s office, clinic, health center, or other place that the individual usually goes to if he/she is sick or needs advice about his/her health” [41]. All outcome variables are self-reported and measured dichotomously.

2.2.2. Independent Variables

2.2.2.1. Community-Level Independent Variables

Two community-level economic and social indicators were included in the current analysis. These indicators were organized by year and geographic area by the lead author and then merged onto the individual-level MEPS data by staff at the Agency for Healthcare Research and Quality (AHRQ).

2.2.2.2. Community-Level Socioeconomic Deprivation

Community-level SES was measured using the ADI (“area-level deprivation”), a 17-item composite indicator at the census block group level [39, 42]. The ADI draws from U.S. census data across domains of education, employment, housing quality, and poverty. The final ADI score assigns a percentile rank for each census block group in the country. A higher rank is associated with greater area-level deprivation. Following the methods used by Kind and Buckingham [39], the ADI was included in the current analysis as quintiles, with the lowest quintile representing the least disadvantaged census block groups.

2.2.2.3. Residential Stability

Residential stability was measured using data from U.S. Census Bureau’s American Community Survey 5-year estimates at the census tract level. Residential stability was operationalized as the percentage of individuals currently living at the same residence they did 1 year prior [31].

2.2.2.4. Individual-Level Sociodemographic and Clinical Variables

In addition to the community-level indicators described above, several individual-level independent variables were included from MEPS data including perceived health status, perceived MH status, MH diagnosis, race and ethnicity, and insurance coverage status.

Both perceived health status and perceived MH status were coded dichotomously with “1” indicating that the individual reported “poor” or “fair” health and “0” indicating “good,” “very good,” or “excellent health.” MH diagnosis was coded as hierarchal, mutually exclusive categories in the order of schizophrenia, bipolar disorder, depressive disorder, and PTSD. Race and ethnicity were coded into the mutually exclusive categories of “White,” “Black or African American,” and Hispanic“” as described above in the Study Sample section. Insurance coverage status included a preconstructed variable from the MEPS data comprised of three categories: “any private coverage” (a respondent reported any private insurance coverage during the study year), “only public coverage” (a respondent reported having only public insurance coverage during the study year), and “uninsured” (the respondent reported being uninsured for the entire study year).

Finally, the multivariable models presented in Table​ 2 were additionally adjusted for a number of demographic variables including sex (only collected as a dichotomous variable by the MEPS), age (coded as a continuous variable), education (coded categorically as less than high-school or G.E.D., high school graduate or G.E.D., or college graduate), marital status (coded dichotomously as living with spouse at time of interview or not), employment status (coded dichotomously as employed at time of interview or not), household poverty status (coded dichotomously as household income below 125% of the federal poverty level (FPL) or at/above 125% FPL), family size (coded categorically as a single person, 2-3 people, or 4+ people), and urban residence (measured dichotomously as living in a census tract classified as “urban” as per the four category rural/urban commuting area (RUCA) codes; [43]).

Table 2. Adjusted models: logistic regressions modeling healthcare access.
Community-level Access to a usual source of care Delayed or forgone healthcare Delayed or forgone prescription medication
OR (SE) p OR (SE) p OR (SE) p
Residential stabilitya 1.10 (0.06) 0.052 0.91 (0.04) 0.034 0.92 (0.05) n.s.
Socioeconomic deprivation
 First quintile (reference) 1.00 n.s. 1.00 1.00
 Second quintile 0.90 (0.14) n.s. 1.00 (0.18) n.s. 1.36 (0.24) n.s.
 Third quintile 1.08 (0.18) n.s. 1.03 (0.17) n.s. 1.46 (0.23) 0.018
 Fourth quintile 1.18 (0.20) n.s. 0.81 (0.14) n.s. 1.30 (0.24) n.s.
 Fifth quintile (most disadvantaged) 0.73 (0.11) 0.050 0.83 (0.14) n.s. 1.16 (0.20) n.s.
  
Individual-level OR (SE) p OR (SE) p OR (SE) p
  
Health fair or poor 1.22 (0.14) n.s. 2.42 (0.25) 0.000 1.89 (0.21) 0.000
MH fair or poor 1.03 (0.10) n.s. 1.54 (0.14) 0.000 1.71 (0.18) 0.000
MH diagnosis
 Schizophrenia (reference) 1.00 1.00 1.00
 Bipolar 0.95 (0.29) n.s. 1.29 (0.38) n.s. 1.49 (0.45) n.s.
 Depression 0.92 (0.25) n.s. 1.18 (0.33) n.s. 1.25 (0.36) n.s.
 PTSD 1.01 (0.37) n.s. 0.56 (0.27) n.s. 1.06 (0.43) n.s.
Race/Ethnicity
 White (reference) 1.00 1.00 1.00
 Black 0.92 (0.11) n.s. 0.62 (0.07) 0.000 0.81 (0.11) n.s.
 Hispanic 0.79 (0.10) n.s. 0.66 (0.08) 0.001 0.63 (0.09) 0.001
Insurance coverage
 Any private coverage (reference) 1.00 1.00 1.00
 Only public coverage 0.84 (0.10) n.s. 1.32 (0.17) 0.034 1.05 (0.12) n.s.
 Uninsured 0.24 (0.03) 0.000 2.12 (0.35) 0.000 1.31 (0.20) n.s.
  • Note: Statistically significant odds ratios appear in bold. All models were additionally adjusted for age, sex, marital status, employment status, poverty status, urban residence, education, and family size. Access to a usual source of care was included as a control variable when modeling delayed or forgone healthcare and delayed or forgone medication.
  • aResidential stability was rescaled 1:10 for inclusion in regression models.

2.3. Statistical Analysis

All analyses were conducted at the AHRQ Datacenter in Rockville, MD using Stata 17. Stata’s suite of “svy” survey commands and Taylor Series Linearization was used to account for the clustering of the MEPS data for this analysis. This approach adjusts standard errors to account for data clustering nested below the MEPS primary sampling unit (PSU) and provides accurate variance estimates for the current analyses [30, 31, 44, 45].

Bivariate (Table 3) and multivariable (Table 2) logistic regression models were used to examine the association between independent variables and healthcare access. The multivariable models are additionally adjusted for the control variables listed in the Methods section. For all regression models, residential stability was rescaled to 1:10 to increase the interpretability of model estimates. So, for example, the odds ratio (OR) for residential stability modeling having a USC in the bivariate analysis presented in Table 3 can be interpreted as “a 10-percentage point increase in residential stability is associated with a 21% increase in the likelihood of having a USC.”

Table 3. Bivariate models: logistic regressions modeling healthcare access.
Access to a usual source of care Delayed or forgone healthcare Delayed or forgone prescription medication
OR (SE) p OR (SE) p OR (SE) p
Residential stabilitya 1.21 (0.06) 0.000 0.88 (0.04) 0.002 0.88 (0.05) 0.021
Socioeconomic deprivation
 First quintile (reference) 1.00 1.00 1.00
 Second quintile 0.87 (0.13) n.s. 1.04 (0.18) n.s. 1.42 (0.24) 0.039
 Third quintile 1.07 (0.17) n.s. 1.17 (0.18) n.s. 1.65 (0.24) 0.001
 Fourth quintile 1.04 (0.16) n.s. 1.09 (0.17) n.s. 1.65 (0.26) 0.002
 Fifth quintile (most disadvantaged) 0.66 (0.09) 0.003 1.20 (0.18) n.s. 1.58 (0.24) 0.003
  • Note: Statistically significant odds ratios appear in bold.
  • aResidential stability was rescaled 1:10 for inclusion in regression models.

3. Results

3.1. Demographic and Clinical Characteristics of Sample

The study sample characteristics can be found in Table 1.

Among the 5444 individuals with MI in the study sample, the mean age was 50.1 years (SD = 16.4), and 32.2% of the sample was male. The majority of the sample met inclusion criteria through a depressive disorder (n = 4670, 85.8%), followed by bipolar disorder (n = 515, 9.5%), schizophrenia and related disorders (n = 139, 2.6%), and PTSD (n = 120, 2.2%). Roughly 61% of the sample reported being non-Latinx White, while 16.6% reported being non-Latinx Black, and 22.5% reported being Latinx.

Overall, 42.1% of the sample reported being employed, 33.1% reported a household income less than 125% of the FPL, and 21% reported having a college degree. Nearly half of the study sample had private insurance coverage while 8.9% of the sample was uninsured. Roughly a third of the sample reported having poor to fair health and MH.

Residential stability, measured as the percentage of individuals in a census tract who had lived in the same residence 1 year prior, had a mean value of 84.4 (SD = 8.2) among census tracts represented by the study sample. In addition, individuals in the study sample were more likely to live in the most socioeconomically disadvantaged communities (22.9%) as compared to the least disadvantaged communities (13.6%).

3.2. Impact of Community-Level Factors on Access to Healthcare

Table 3 presents results from the bivariate logistic regression models, and Table 2 presents results from the multivariable logistic regression models.

Higher levels of community-level residential stability were associated with greater odds of having access to a USC in bivariable models (Table 3; OR = 1.21, p < 0.001), though this association diminished in the adjusted models (Table 2; OR = 1.10, p = 0.052). Inversely, higher levels of community-level residential stability were associated with decreased odds of delaying or forgoing healthcare in bivariate models (Table 3; OR = 0.88, p < 0.01) and delaying or forgoing prescription medication (Table 3; OR = 0.88, p < 0.05). Residential stability remains a significant predictor of delayed or forgone healthcare in the adjusted models (Table 2; OR = 0.91, p < 0.05).

In bivariate models, living in the most socioeconomically deprived communities (quintile 5) was associated with the lower odds of having a usual source compared to living in the least deprived (quintile 1) communities (Table 3; OR = 0.66, p < 0.01); however, this association diminished in the multivariable model (Table 2; OR = 0.73, p = 0.050). Compared to individuals living in the least socioeconomically deprived communities (quintile 1), individuals in the second through fifth quintiles were more likely to delay or forgo prescription medication in the bivariate models (Table 3; ORs 1.42–1.65, p < 0.05). This association remained significant for the third socioeconomic quintile compared to the first (least deprived) quintile in the fully adjusted model (Table 2; OR = 1.46, p < 0.05).

3.3. Impact of Individual-Level Factors on Healthcare Access

Multivariable models in Table 2 show that both self-reported physical and MH were significant predictors of healthcare access among individuals in the study sample. Specifically, individuals who reported poor or fair physical health had higher odds of delaying or forgoing healthcare (OR = 2.42, p < 0.001) and delaying or forgoing prescription medication (OR = 1.89, p < 0.001) compared to individuals who reported their physical health to be good, very good, or excellent. Likewise, individuals who reported poor or fair MH were also more likely to report delaying or forgoing healthcare (OR = 1.54, p < 0.001) and delaying or forgoing prescription medication (OR = 1.71, p < 0.001) than individuals who reported their MH to be good, very good, or excellent.

Individuals in the sample who identified as Black had lower odds of delayed or forgone healthcare than their White counterparts (OR = 0.62, p < 0.001). Similarly, individuals who identified as Hispanic had lower odds of delaying or forgoing healthcare and prescription medication as compared to their White counterparts (ORs = 0.66 and 0.63, respectively, p < 0.01). Individuals who had only public insurance coverage during the study period were more likely than individuals who had any private insurance coverage to have delayed or forgone healthcare (OR = 1.32, p < 0.05). Individuals who were uninsured for the entire study period were only a quarter as likely to have a USC (OR = 0.24, p < 0.001) and more than twice as likely to have delayed or forgone healthcare (OR = 2.12, p < 0.001) compared to individuals who had any private insurance coverage.

4. Discussion

In the U.S., individuals with MI must often navigate fragmented systems of care to get their physical and MH needs met [21]. Unfortunately, many barriers exist that prevent these individuals from receiving adequate care, which can result in poor health and healthcare outcomes [46, 47]. While previous studies have extensively examined the individual-level factors that can help or hinder access to care, few studies have examined how the characteristics of the communities in which people with MI live influence healthcare access and utilization [25].

The current study found that, among a sample of adults with MI, community-level socioeconomic disadvantage was associated with less access to a USC and decreased access to prescription medication. Residential stability within the community was associated with increased access to a USC, decreased odds of delaying and forgoing needed care, and decreased odds of forgoing prescription medication. The association between residential stability and delaying or forgoing needed care remained significant even after including individual-level variables.

Findings from the current study lend support to a growing body of literature that suggests socioeconomic disadvantage at the community level hinders individuals with MI from accessing healthcare. First, a heightened need for care in disadvantage neighborhoods may be driven by a myriad of community-level social and economic characteristics that research has found to be potent social determinants of health [4850]. Secondly, as Davidson et al. [12] theorize, poorer communities may struggle to retain quality care providers due to high rates of publicly and uninsured individuals. This may disproportionately impact individuals with MI who rely on safety net providers to get their mental and physical healthcare need met [12, 51]. A lack of available quality care, in turn, may exacerbate mental and physical health symptomatology which then increases both the need and demand for care [52].

Findings from the current study also suggest that residential stability can help keep individuals with MI linked to a USC and is a protective factor against delaying or forgoing needed care. One possible explanation for these findings is that residential stability helps to maintain healthy social networks and support systems at the community level. Healthy social networks and support systems act as a protective factor against community stressors that may otherwise negatively affect health and healthcare outcomes [53]. Social networks may also be an important mechanism through which information about health and healthcare services is shared among individuals within a community, and strong social networks may help contribute to norms and attitudes that facilitate treatment seeking, access, and engagement [38].

Interestingly, Black and Hispanic individuals in the current study reported less difficulty accessing care than their White counterparts. While racial and ethnic disparities in access to care are well documented in the literature, previous studies also suggest that social networks and social support systems, particularly among Black and Latinx communities, can influence the perceived need for care and the willingness of individuals to initiate care and serve as an informal source of care [36, 37, 54, 55]. At the systems level, disproportionately low rates of contact with providers may also contribute to low levels of perceived need for care among Black and Latinx individuals [28]. The way in which community-level factors may differentially impact healthcare access for individuals with MI based on race and ethnicity is an area for future research.

Finally, the U.S. has been relatively slow to develop and incorporate empirically sound, standardized measures of community-level social and economic characteristics into health and healthcare data. Phillips et al. [56] drew attention to this fact in their article titled, “How Other Countries Use Deprivation Indices—And Why the United States Desperately Needs One.” The authors note that, for decades, countries like New Zealand and the United Kingdom (among others) have been using such measures to “assess community needs, inform research, adjust clinical funding, allocate community resources, and determinate policy impact” (p. 1). Fortunately, some recent progress has been made in the U.S. For example, the development and validation of an updated ADI, used in the current study, has been funded by the National Institute of Health and recently made available to the public [39]. Though it remains one of the only validated, multidimensional tools of its kind in the U.S., the utility of the ADI is evident in its increasingly widespread use in health services research and, more recently, its incorporation by the Centers for Medicare and Medicaid (CMS) Innovation into risk adjustment benchmarks [57]. While these advancements are promising, the continued development and use of such indices in the U.S. is needed to progress health equity frameworks and policies aimed at equitably allocating healthcare resources, improving population health, and decreasing health disparities, particularly among vulnerable groups including individuals with MI [57].

Toward this end, the current study specifically illustrates how community-level characteristics can be used to augment existing health and healthcare data in the U.S., creating a more holistic picture of the factors that influence an individual’s ability to access healthcare. As community-level characteristics have been increasingly recognized as important drivers of health and healthcare access, new opportunities to develop and deploy community-minded interventions are beginning to emerge in the U.S. For example, in 2021, the CMS announced that it would assist states in funding and delivering interventions aimed at addressing health-related social needs (HRSNs), which are envisioned as an extension of an individual’s social determinants of health such as nutrition, housing, transportation, neighborhood safety, social networks, and educational and employment opportunities [58]. Findings from the current study support the development of programs that both target community-level social and economic factors directly as well as interventions that are responsive to an individual’s social and economic environment when trying to optimize access to healthcare. The current study also highlights the potential of community-level social and economic indicators in helping identify the individuals and communities that might most benefit from the allocation of these additional resources and supports. As future research establishes the evidence base in this emerging area, researchers and policymakers will need to be intentional in considering the unique healthcare needs and community contexts of individuals with MI, for whom community-level social and economic forces may be particularly potent predictors of healthcare access.

5. Limitations and Future Directions

Findings from the current analysis should be considered within the context of several limitations. First, while the data are drawn from a nationally representative sample, these analyses did not use the MEPS person-level weights, which means that estimates may not be representative of the entire U.S. population. Sample weights in the MEPS data do not accommodate studies that use only a single panel for each year of MEPS data—as is the case when establishing diagnoses (in each respondent’s first year in MEPS) before outcomes are examined (in each respondent’s second year in MEPS).

Second, the most common MH diagnoses in the study sample were depressive disorders. While we acknowledge the pitfalls of trying to categorize MH diagnoses into distinct groups, future research should replicate these analyses with individuals who have MH diagnoses associated with higher levels of service need, such as schizophrenia and other psychotic disorders.

Third, the findings from the current analyses carry forward the same limitations inherent in the community-level data that were compiled to make the current study possible. Notably, geographic boundaries used across these datasets are defined by the federal government and may not reflect the true social, economic, and structural communities with which individuals in the study routinely interact [59]. On a related note, both access to healthcare and community dynamics are likely to vary significantly between geographic locations, including between urban and rural areas. As the current study included a sample of individuals primarily residing in urban areas (85.1%), our findings may not be generalizable to rural contexts. Future research is needed to examine how geographic context impacts the differences found in both access to care as well as community characteristics.

Fourth, our findings and conclusions are limited by the broad definitions, carried forward from the MEPS data, that were used to capture access to healthcare. Replicating these analysis using a more granular definition of access to care, and incorporating indicators of actual service use, would help strengthen the current body of literature.

Fifth, while the ADI provides a robust multidimensional measure of community-level socioeconomic disadvantage in the U.S., no such measure exists for residential stability. As such, the current study used a single unidimensional indicator of residential stability from U.S. census data which is likely limited in its ability to capture the complexities and nuances of this construct. Establishing a standardized measure of community-level residential stability in the U.S. is an area for future research.

Finally, the current study used relatively broad insurance coverage categories that limited our ability to provide a more detailed analysis of how healthcare access among individuals with MI is impacted by specific types of healthcare coverage and programs. The financing and delivery of both physical and mental healthcare in the U.S. is comprised of a complex patchwork of policies, involving both public and private insurers and providers, which change over time and vary between localities. For example, Medicaid, the largest payee of behavioral health services in the U.S., gives states vast discretion in determining program eligibility, the types of services covered, and how behavioral health services are administered and delivered [6062]. While providing a comprehensive review of healthcare policy in the U.S. is beyond the scope of this paper, future research is needed that examines how community characteristics and access to healthcare are simultaneously shaped by healthcare policy, financing, and delivery at the local, state, and federal levels.

6. Conclusion

Findings from the current study suggest that community-level social and economic factors influence healthcare access and utilization among individuals with MI. Therefore, interventions and policies must consider individuals with MI within the context of their broader environments when trying to increase access to and engagement in healthcare services [12, 25].

Disclosure

The analysis presented in this manuscript is a continuation of work submitted to fulfill the dissertation requirements of the Ph.D. in Social Work program at the University of North Carolina at Chapel Hill (see [63]). The full dissertation can be found here: https://doi.org/10.17615/kp23-1603.

Conflicts of Interest

The authors declare no conflicts of interest.

Funding

No funding was received for this manuscript.

Appendix A: ICD-9 and ICD-10 Codes Used to Identify Mental Health Conditions

Table A1. ICD-9 and ICD-10 codes used to identify eligible mental health conditions in the MEPS conditions files.
Diagnosis ICD Codes
Schizophrenia and related disorders ICD-9 293.81, 293.82, 295.xx, 297.xx, 298.xx, 301.22
ICD-10 F06.0x, F06.2x, F20.xx–F25.xx, F28.xx, F29.xx
  
Bipolar disorder ICD-9 296.0x, 296.1x, 296.4x–296.7x, 296.80, 296.81, 296.89, 301.10, 301.13
ICD-10 F30.xx, F31.xx, F34.0x
  
Depressive disorders ICD-9 296.2x, 296.3x, 300.4x, 301.12, 309.1x, 311.xx
ICD-10 F32.0x–F32.5x, F32.9, F33.0x–F33.4x, F33.9
  
Posttraumatic stress disorder ICD-9 309.81
ICD-10 F43.1x
  • Note: Diagnostic codes were compiled from the Clinical Classification Software and the Diagnostic Code Set General Equivalence Mappings.

Data Availability Statement

Research data are not shared.

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