Kaplan-Meier survival curves are adjusted for age, sex, cancer type, urban location, Charlson Comorbidity Index score, and the interaction between sex and cancer type (nonexpansion states before vs after expansion, hazard ratio, 1.01; 95% CI, 0.99-1.02; P = .43; expansion states before vs after expansion, hazard ratio, 0.98; 95% CI, 0.97-0.99; P = .008).
eAppendix 1. Definition of First Cancer Diagnosis
eTable 1. National Cancer Database Medicaid Expansion Status Variable
eAppendix 2. Definition of Race Variable
eFigure 1. Population Flowchart
eTable 2. Baseline Trend for DID Assumption
eTable 3. Baseline Characteristics for Pre- and Post-Expansion Groups
eTable 4. Cox Regression by Cancer Type
eFigure 2. Forest Plot of Hazard Ratios by Vulnerable Population
eTable 5. Cox Regression by Early and January 2014 Expansion Groups
eTable 6. Cox Regression of Patients with Missing/Unknown Stage
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Lam MB, Phelan J, Orav EJ, Jha AK, Keating NL. Medicaid Expansion and Mortality Among Patients With Breast, Lung, and Colorectal Cancer. JAMA Netw Open. 2020;3(11):e2024366. doi:10.1001/jamanetworkopen.2020.24366
Is Medicaid expansion associated with changes in mortality for patients with cancer?
In this cross-sectional study of 523 802 patients with newly diagnosed breast, colorectal, or lung cancer, Medicaid expansion was associated with decreased mortality in expansion states compared with control nonexpansion states. This mortality improvement appeared to be mediated by earlier stage of cancer at diagnosis.
In this study, Medicaid expansion was associated with a decreased hazard of mortality among patients with newly diagnosed breast, colorectal, and lung cancer.
Medicaid expansion under the Patient Protection and Affordable Care Act may be associated with increased screening and may improve access to earlier treatment for cancer, but its association with mortality for patients with cancer is uncertain.
To determine whether Medicaid expansion is associated with improved mortality among patients with cancer.
Design, Setting, and Participants
This is a quasi-experimental, difference-in-difference (DID), cross-sectional, population-based study. Patients in the National Cancer Database with breast, lung, or colorectal cancer newly diagnosed from January 1, 2012, to December 31, 2015, were included. Data analysis was performed from January to May 2020.
Living in a state where Medicaid was expanded vs a nonexpansion state.
Main Outcomes and Measures
The main outcome was mortality rate according to whether the patient lived in a state where Medicaid was expanded.
A total of 523 802 patients (385 739 women [73.6%]; mean [SD] age, 54.8 [6.5] years) had a new diagnosis of invasive breast (273 272 patients [52.2%]), colorectal (111 720 patients [21.3%]), or lung (138 810 patients [26.5%]) cancer; 289 330 patients (55.2%) lived in Medicaid expansion states, and 234 472 patients (44.8%) lived in nonexpansion states. After Medicaid expansion, mortality significantly decreased in expansion states (hazard ratio [HR], 0.98; 95% CI, 0.97-0.99; P = .008) but not in nonexpansion states (HR, 1.01; 95% CI, 0.99-1.02; P = .43), resulting in a significant DID (HR, 1.03; 95% CI, 1.01-1.05; P = .01). This difference was seen primarily in patients with nonmetastatic cancer (stages I-III). After adjusting for cancer stage, the mortality improvement in expansion states from the periods before and after expansion was no longer evident (HR, 1.00; 95% CI, 0.98-1.02; P = .94), nor was the difference between expansion vs nonexpansion states (DID HR, 1.00; 95% CI, 0.98-1.02; P = .84).
Conclusions and Relevance
Among patients with newly diagnosed breast, colorectal, and lung cancer, Medicaid expansion was associated with a decreased hazard of mortality in the postexpansion period, which was mediated by earlier stage of diagnosis.
The Patient Protection and Affordable Care Act expanded Medicaid eligibility to nonelderly adults with incomes at or below 138% of the federal poverty level in participating states. By March 2020, 36 states and Washington, DC, had expanded Medicaid,1 with more than 20 million US residents obtaining coverage.2
Previous studies among patients with cancer have shown Medicaid expansion to be associated with fewer patients being uninsured, increased screening,3 and earlier stage of diagnosis,4-11 with mixed results on racial and socioeconomic disparities.12-15 Studies have shown increased colorectal cancer screening among low-income and Black patients within early expansion states.13 Medicaid expansion is also associated with reduced racial disparities in access to high-volume hospitals for cancer surgery and increased rates of cancer surgery among low-income patients. However, it is also associated with increased racial disparity in access to high-quality hospitals for cancer surgery.12,15 The association of Medicaid expansion with mortality for patients with cancer remains unknown. Medicaid expansion might improve mortality through earlier detection, earlier stage of diagnosis, and/or improved access to recommended treatments. Alternatively, expansion could worsen mortality by overloading the oncology workforce and hospitals16,17 with an influx of newly covered patients, leading to increased wait times seen in other settings.18,19 As nonexpansion states engage in ongoing discourse about whether to expand Medicaid, empirical data would be helpful in guiding their decisions.
In this study, we sought to build on the data showing that Medicaid expansion increased detection of early-stage cancer by examining 3 questions. First, did mortality for patients with cancer change in states that expanded Medicaid compared with states that did not expand Medicaid? Second, if there were changes, could detection at earlier stage be mediating those changes? Finally, did similar mortality changes occur among at-risk populations (ie, patients living in lowest income neighborhoods and Black vs White patients)?
Data were obtained from the National Cancer Database (NCDB), which contains patient-level data on more than 70% of new cancer diagnoses from approximately 30% of US hospitals. The Harvard University institutional review board approved this study and waived the need for informed consent because the data are publicly available and deidentified. This study follows the Strengthening the Reporting of Observational Studies in Epidemiology (STROBE) reporting guideline.20
We studied patients with newly diagnosed invasive breast, colorectal, and lung cancer from January 1, 2012, to December 31, 2015. We only included patients for whom this was their first cancer diagnosis (eAppendix 1 in the Supplement). These cancers were selected because they are common, amenable to screening, and treated for cure in the nonmetastatic setting. Outcomes for these patients could be sensitive to changes in insurance and access to care. A recent study9 found that expansion states had a higher rate of patients whose cancer was diagnosed at an earlier stage compared with nonexpansion states after Medicaid expansion for these cancers. NCDB provides a variable indicating the expansion status of each patient’s state of residence. We classified expansion states as early (ie, before the Patient Protection and Affordable Care Act) and as January 2014 (eTable 1 in the Supplement) to compare with the nonexpansion group. We excluded patients in late expansion states (mid-2014 to 2018 expansion) because we could not determine the time of expansion without additional information (state of residence) and had insufficient postexpansion data. We also excluded patients for whom NCDB did not report expansion status (missing or aged <40 years). We excluded patients with missing data on insurance status or cancer stage (26 819 patients [4.9%]). eFigure 1 in the Supplement depicts the population flowchart.
The primary outcome was mortality, which is defined in the NCDB as months from initial cancer diagnosis to death. Information on cancer-specific mortality is not available in NCDB. Twenty-four states and the District of Columbia expanded their Medicaid programs on January 1, 2014, which marked the beginning of the postexpansion period in our primary analysis (eTable 1 in the Supplement). Early expansion states formally expanded on January 1, 2014, but a smaller subset could join Medicaid earlier through a waiver process. We included these states in our analyses, understanding that they could bias our results toward the null.
We first summarized baseline characteristics of our cohort in expansion (early and January 2014) and nonexpansion states. Missing data were presented for zip code–level variables and were included as a separate category. Our primary Cox proportional hazards model compared the change in survival times—from the periods before to after expansion—between patients in expansion and nonexpansion states. The outcome, survival, was available for patients whose cancer was diagnosed by December 31, 2015. The primary independent variables in the model were expansion status (expansion vs nonexpansion), period (before expansion [2012-2013] vs after expansion [2014-2015]), and the interaction between expansion status and period. Significance of the difference-in-difference (DID) interaction term indicates that the change in survival over time in expansion states was different from the change in survival over time in nonexpansion states.
Our primary model and corresponding adjusted Kaplan-Meier curves were adjusted for age, sex, cancer type, urban location, Charlson Comorbidity Index score, and the interaction between sex and cancer type. Variables were categorized as shown in Table 1. We did not adjust for cancer stage or other patient characteristics (education, income, insurance, and race) that could have acted as mediators of Medicaid expansion. Race categories were defined per the NCDB (eAppendix 2 in the Supplement). To determine the role of intermediary variables, our second model adjusted for education, income, insurance, and race. Our final model also adjusted for stage.
Secondary models were stratified by cancer stage (stages I-III vs stage IV), cancer type, and at-risk subpopulations (ie, lowest vs highest quartiles of median household income by zip code, and Black vs White patients). We present the stratified results for these subgroups because they were a priori of clinical interest: 3-way interactions with income, race, and cancer type were not statistically significant, indicating similar changes in each set of subgroups. The 3-way interaction with stage was statistically significant. All analyses were performed from January to May 2020 using SAS statistical software version 9.4 (SAS Institute). For our primary analysis of the DID between expansion vs nonexpansion states, a 2-sided P < .05 was considered statistically significant. P values for secondary analyses should be interpreted with caution because multiple testing may produce false-positive findings. Baseline mortality trends (comparing mortality changes in preexpansion years 1 and 2 between expansion and nonexpansion states) were similar (eTable 2 in the Supplement).
For the main model, we performed sensitivity analyses examining the consistency of results separately for early and January 2014 expansion states. We ran a second set of sensitivity analyses including patients with unknown cancer stage.
We identified 523 802 patients aged 40 to 64 years (385 739 women [73.6%]; mean [SD] age, 54.8 [6.5] years) with newly diagnosed invasive breast (273 272 patients [52.2%]), colorectal (111 720 patients [21.3%]), or lung (138 810 patients [26.5%]) cancer from 2012 to 2015 (eFigure 1 in the Supplement). There were 234 472 patients (44.8%) in nonexpansion states and 289 330 patients (55.2%) in Medicaid expansion states (Table 1). Most patients were White individuals and lived in an urban location. Compared with expansion states in the preexpansion period, a higher proportion of patients in nonexpansion states were uninsured (4.2% [2060 patients] in early expansion states and 5.1% [4671 patients] in 2014 expansion states vs 10.1% [11 584 patients] in nonexpansion states), were in the lowest quartile of median income by zip code (6.8% [3336 patients] in early expansion states and 15.9% [14 563 patients] in 2014 expansion states vs 25.0% [28 673 patients] in nonexpansion states), and were in the lowest quartile of education by zip code (percentage having less than a high school education, 17.6% [8634 patients] in early expansion states and 15.1% [13 831 patients] in 2014 expansion states vs 23.2% [26 609 patients] in nonexpansion states) (eTable 3 in the Supplement).
Kaplan-Meier adjusted survival curves (Figure) and an adjusted Cox regression model (Table 2) show a small but significant mortality improvement in expansion vs nonexpansion states. The Kaplan-Meier absolute survival difference was 0.4% (meaning that 250 patients with cancer would need to gain coverage for 1 death to be prevented 4 years after cancer diagnosis). There was a statistically significant 2.0% decreased hazard of death (hazard ratio [HR], 0.98; 95% CI, 0.97-0.99; P = .008) in the expansion group from the preexpansion to postexpansion periods; if this 2.0% reduction in mortality were realized in all Medicaid expansion states, then among the 69 000 patients with cancer diagnosed, 1384 lives would be saved yearly. In contrast, mortality was unchanged in nonexpansion states over time (HR, 1.01; 95% CI, 0.99-1.02; P = .43). The DID ratio comparing the HRs in nonexpansion states with expansion states indicates that the improved mortality in expansion states was significantly different from the unchanged mortality in nonexpansion states (DID HR, 1.03; 95% CI, 1.01-1.05; P = .01). In general, a DID HR greater than 1 indicates a greater improvement in expansion vs nonexpansion states or less worsening in expansion vs nonexpansion states.
Stratifying by cancer type, similar trends persisted, with expansion states having better changes over time compared with nonexpansion states (eTable 4 in the Supplement). For lung cancer, mortality improved in both expansion states (HR, 0.94; 95% CI, 0.93-0.96; P < .001) and nonexpansion states (HR, 0.97; 95% CI, 0.95-0.99; P = .003), but the improvement was significantly greater in expansion than in nonexpansion states (DID HR, 1.03; 95% CI, 1.00-1.06; P = .03). For breast and colorectal cancers, mortality was worse in both expansion and nonexpansion states. Although the degree to which mortality increased was lower in expansion states, the difference between the HRs was not significantly different for breast cancer (DID HR, 1.04; 95% CI, 0.98-1.10; P = .24) or colorectal cancer (DID HR, 1.04; 95% CI, 1.00-1.09; P = .08).
To determine the association of intermediary variables with the decreased hazard of death, we first adjusted for education, income, insurance, and race. After adjusting for these variables, the mortality reduction persisted from the preexpansion and postexpansion periods for expansion states (HR, 0.98; 95% CI, 0.96-0.99; P = .006). Similarly, there was greater improvement in mortality in expansion vs nonexpansion states, which also remained significant (DID HR, 1.05; 95% CI, 1.02-1.07; P < .001). However, after adjusting also for cancer stage, there were no longer any reductions in mortality over time for expansion states (HR, 1.00; 95% CI, 0.98-1.02; P = .94). The difference between expansion and nonexpansion states in the change in the hazard of death was no longer significant after adjusting for cancer stage (DID HR, 1.00; 95% CI, 0.98-1.02; P = .84) (Table 2), suggesting that survival differences were mediated by cancer stage.
For patients with stages I to III (nonmetastatic) cancer, there was a significant 4.8% increased hazard of death in nonexpansion states (HR, 1.05; 95% CI, 1.02-1.08; P < .001) and unchanged mortality in expansion states from the preexpansion to postexpansion period (HR, 0.99; 95% CI, 0.97-1.02; P = .64) (Table 3). There was significantly improved mortality in expansion vs nonexpansion states (DID HR, 1.05; 95% CI, 1.02-1.09; P = .003). For patients with stage IV (metastatic) cancer, both expansion and nonexpansion states had mortality improvements, but the differences were not significant. The association of Medicaid expansion was significantly different among patients with stages I to III cancer compared with patients with stage IV cancer (3-way DID HR, 1.05 [95% CI, 1.02-1.09] for stages I-III vs 0.98 [95% CI, 0.95-1.00] for stage IV; P = .002).
Among patients living in areas with the lowest quartile of median household income, mortality was unchanged within nonexpansion states (HR, 1.00; 95% CI, 0.97-1.03; P = .91) and decreased only slightly and not significantly for expansion states over time (HR, 0.99; 95% CI, 0.95-1.02; P = .43) (Table 4 and eFigure 2 in the Supplement). These mortality changes were not significantly different (DID HR, 1.02; 95% CI, 0.97-1.06; P = .48). Among patients living in areas with the highest quartile of median household income, mortality increased slightly but not significantly within nonexpansion states (HR, 1.03; 95% CI, 0.99-1.07; P = .19) and decreased slightly but not significantly within expansion states (HR, 0.98; 95% CI, 0.96-1.01; P = .23); again, the mortality changes were not significantly different (DID HR, 1.04; 95% CI, 1.00-1.09; P = .07). Medicaid expansion was not associated with a difference in mortality among patients in the lowest vs highest quartile of median household income (DID HR, 1.02 [95% CI, 0.97-1.06] for the lowest quartile vs 1.04 [95% CI, 1.00-1.09] for the highest quartile; P = .49).
For Black patients, mortality decreased slightly but not significantly in expansion states (HR, 0.97; 95% CI, 0.93-1.01; P = .10) and was unchanged in nonexpansion states (HR, 1.00; 95% CI, 0.97-1.04; P = .95) from the preexpansion to postexpansion period. These mortality change differences were not significant (DID HR, 1.04; 95% CI, 0.98-1.09; P = .19), although the small samples sizes limited statistical power. For White patients, mortality was slightly but not significantly lower in expansion states (HR, 0.99; 95% CI, 0.97-1.01; P = .17) and slightly but not significantly higher in nonexpansion states (HR, 1.02; 95% CI, 1.00-1.04; P = .09). However, these mortality changes were significantly different in the DID analysis (DID HR, 1.03; 95% CI, 1.00-1.05; P = .03). Medicaid expansion was not associated with a difference in mortality between Black vs White patients (DID HR, 1.04 [95% CI, 0.98-1.09] for Black patients vs 1.03 [95% CI, 1.00-1.05] for White patients; P = .74).
With our first sensitivity analysis, we stratified expansion states into early and January 2014 groups (eTable 5 in the Supplement). The DID ratio comparing HRs in nonexpansion vs early expansion states indicated that the improved mortality in the early expansion states was significantly different from the unchanged mortality in nonexpansion states (DID HR, 1.04; 95% CI, 1.01-1.07; P = .01). Similarly, there was improved mortality in the January 2014 expansion states compared with nonexpansion states, although the difference was not significant (DID HR, 1.02; 95% CI, 1.00-1.05; P = .08). We ran a second set of sensitivity analyses including patients with unknown stage, and the findings were consistent with our primary findings (eTable 6 in the Supplement).
In this national study of patients with invasive breast, colorectal, and lung cancer, Medicaid expansion was associated with a significant decrease in mortality in expansion states compared with nonexpansion states. The decreased mortality may be due to increases in early-stage diagnosis associated with better access to screening and early diagnosis of cancer. There were no differences in mortality changes among at-risk populations, including among Black patients and among those living in areas with the lowest quartile of income.
There are several factors that could explain improved mortality associated with Medicaid expansion. Prior research9 demonstrated a small but significant increase in early-stage diagnoses in expansion states compared with nonexpansion states. Our analyses that omitted and then included cancer stage suggest a plausible association wherein earlier stage at diagnosis appears to explain the mortality improvement. Increased Medicaid coverage may remove barriers to accessing the health care system for screening and timely symptom evaluation, especially because we typically consider insurance coverage as an immediate change once implemented. The lower mortality in expansion states compared with nonexpansion states was similar across all 3 cancer types, although in stratified analyses, the difference was significant only for lung cancer. Lung cancer has a higher mortality rate than breast and colorectal cancer, and with longer follow-up, it is possible that the lower mortality rates seen for breast and colorectal cancer may also become significant. In addition, in the US, it appears that there has been a dramatic improvement in lung cancer mortality during this period, whereas the improvements in breast and colorectal cancer mortality have slowed over the years.21
Prior studies22,23 of Medicaid expansion in 2000 and Massachusetts health reform in 2006 demonstrated lower death rates after expansion. In the 2000 Medicaid expansion study,22 the authors estimated that 1 death was prevented for every 239 to 316 adults who gained coverage, whereas the Massachusetts 2006 health reform study23 found 1 death per year prevented for 830 adults who gained coverage. In the present study, on the basis of the Kaplan-Meier absolute survival difference of 0.4%, we estimate that 250 patients with cancer would need to gain coverage for 1 death to be prevented 4 years after cancer diagnosis. Moreover, if the 2.0% absolute reduction in mortality were realized in all Medicaid expansion states (early and January 2014 expansion states), then among the approximately 69 000 patients with cancer diagnosed, 1384 lives would be saved yearly. Although the comparisons are not straightforward given the different populations and periods, this provides a concrete sense of lives saved by Medicaid coverage for patients with cancer.
When we examined the mortality among patients with curable (stages I-III) and metastatic (stage IV) cancer, we saw a significant mortality improvement in expansion states for patients with curable cancer but not those with metastatic cancer after Medicaid expansion. Interestingly, mortality in the metastatic cohort improved similarly for both expansion and nonexpansion states. It is possible that increased development and use of immunotherapies has decreased mortality in most of these groups over time, especially in the metastatic setting, for which most immunotherapies are initially tested and approved.24 Also, with increased focus and attention on palliative care, it is possible that patients with metastatic disease are receiving better end-of-life care25 in both expansion and nonexpansion states.
Although the main goal of our study was to understand the mortality difference between expansion and nonexpansion states after expansion, we saw a baseline mortality difference between the 2 groups, with patients with cancer in nonexpansion states having a higher hazard of death; this preexisting mortality gap persisted in the postexpansion period. Potential hypotheses include differences in social support, social determinants of health, or limited health resources. Both expansion and nonexpansion states saw an increase in the total number of patients with breast, colorectal, or lung cancer from the preexpansion to postexpansion period. However, it is possible that expansion states were better prepared for the increase in patients given advanced notice of expanding Medicaid and anticipating a potential increase in patients using hospital resources. Additional studies are warranted to further understand these baseline differences.
Any new policy may result in unintended consequences, especially for at-risk populations. Prior studies have highlighted disparities in outcomes for patients with cancer.26-28 We were reassured to find that patients in areas in the lowest quartile of median household income within expansion states showed a modest, nonsignificant decrease in mortality after expansion. We also observed that mortality improvements associated with Medicaid expansion did not differ for Black vs White patients.
Our work adds to a limited body of evidence on Medicaid expansion and cancer care. A few studies have shown that among patients with cancer, expansion was associated with increased insurance coverage,6,9,29 earlier stage of diagnosis,9,30,31 and no changes in timeliness of treatment.9,32 Although some studies33,34 have investigated the association of Medicaid expansion with mortality for some disease processes (ie, end-stage renal disease or cardiovascular disease), to our knowledge, there are no studies that investigate the association between Medicaid expansion and cancer mortality.
There are several limitations of our study. First, this is an observational study. Randomized clinical trials of new policies are often difficult to implement. We attempted to minimize unmeasured confounding by using a DID analysis. Second, we lacked patient-level information regarding several variables, including individuals’ state of residence or eligibility for Medicaid, meaning that we were unable to control for state-level fixed effects, income, and education. Third, our study focused on patients with breast, colorectal, and lung cancer aged 40 to 64 years. This could limit the generalizability of our data, although few patients with cancers of these types receive a diagnosis before age 40 years. Fourth, we examined time to death, which is subject to lead-time bias if increases in screening preferentially detect slower-growing tumors. However, when analyzing mortality by cancer type, we found that although all groups had lower mortality within expansion vs nonexpansion states, those with breast and colorectal cancer saw a slight decrease in time to death over time (in both expansion and nonexpansion groups), which would not be consistent with our findings being explained by increases in cancer screening. Furthermore, longer follow-up would be helpful to understand whether this mortality improvement persists.
This cross-sectional study found that Medicaid expansion was associated with improved mortality in patients with newly diagnosed breast, lung, and colorectal cancers. This association appeared to be mediated by earlier stage of cancer diagnosis and did not differ by race or area-level income.
Accepted for Publication: September 8, 2020.
Published: November 5, 2020. doi:10.1001/jamanetworkopen.2020.24366
Open Access: This is an open access article distributed under the terms of the CC-BY License. © 2020 Lam MB et al. JAMA Network Open.
Corresponding Author: Miranda B. Lam, MD, MBA, Department of Radiation Oncology, Brigham and Women’s Hospital, Dana-Farber Cancer Institute, 75 Francis St, Boston, MA 02446 (firstname.lastname@example.org).
Author Contributions: Dr Lam had full access to all of the data in the study and takes responsibility for the integrity of the data and the accuracy of the data analysis.
Concept and design: Lam, Jha, Keating.
Acquisition, analysis, or interpretation of data: All authors.
Drafting of the manuscript: Lam.
Critical revision of the manuscript for important intellectual content: All authors.
Statistical analysis: Lam, Phelan, Orav, Keating.
Obtained funding: Lam.
Administrative, technical, or material support: Lam.
Supervision: Lam, Jha.
Conflict of Interest Disclosures: None reported.
Funding/Support: This work was conducted with the support of award KL2 TR002542 from Harvard Catalyst, The Harvard Clinical and Translational Science Center, and National Center for Advancing Translational Sciences, National Institutes of Health.
Role of the Funder/Sponsor: The sponsors had no role in the design and conduct of the study; collection, management, analysis, and interpretation of the data; preparation, review, or approval of the manuscript; and decision to submit the manuscript for publication.
Disclaimer: The content is solely the responsibility of the authors and does not necessarily represent the official views of Harvard Catalyst, Harvard University and its affiliated academic health care centers, or the National Institutes of Health.
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