Dr. Kaplan is now Director of the Office of Behavioral and Social Sciences Research (OBSSR) at NIH.
To test the hypotheses that reported asthma prevalence is higher among insured than uninsured children and that insurance-based differences in asthma diagnosis, treatment, and healthcare utilization are associated with disease severity.
National Health and Nutrition Examination Survey, 2003–2008.
We used multivariate logistic regression to examine the relationship between insurance and asthma symptom severity with asthma diagnosis, treatment, and acute care utilization.
In multivariate analysis, insured children had greater odds of reporting a current diagnosis of asthma than uninsured children (Odds Ratio [OR]=2.08, 95% Confidence Interval [CI] 1.47–2.94). When interactions between insurance and asthma impairment were included, insurance was associated with greater odds of diagnosis among children with intermittent (OR=4.08, 95%CI 1.57–10.61), but not persistent, symptoms. Among children with intermittent symptoms, insurance was associated with inhaled corticosteroid use (OR=4.51, 95%CI 1.18–17.24) and asthma-related acute care utilization (OR=5.21, 95%CI 1.21–23.53); these associations were non-significant among children with persistent symptoms.
Being insured increases only the likelihood that a child with intermittent, not persistent, asthma symptoms will receive an asthma diagnosis and control medication, and may not reduce acute care utilization. Although universal insurance may increase detection and management of undiagnosed childhood asthma, theorized cost savings from reduced acute care utilization might not materialize.
Providing health insurance to uninsured children with known asthma can result in improved asthma outcomes, including fewer asthma attacks and less frequent asthma-related hospitalizations and emergency department (ED) visits (
The Children’s Health Insurance Program Reauthorization Act (CHIPRA) and the Affordable Care Act (ACA) may lead to a large number of uninsured children becoming insured (
Even if insurance status does increase the chance of an asthma diagnosis, whether that diagnosis leads to reduced asthma-related acute care utilization (i.e., acute care for exacerbation of asthma symptoms) is unclear. Previous studies have documented lower rates of ED and physician visits for wheezing, and fewer missed school days among undiagnosed symptomatic children compared with diagnosed asthmatic children (
The purpose of this study was to examine the differences in asthma diagnosis and outcomes among children with and without insurance, and to determine the association between health insurance and asthma diagnosis, impairment level, and asthma-related outcomes among children with asthma symptoms. Accounting for factors known to be associated with asthma prevalence (e.g., race/ethnicity), we hypothesized that uninsured children would have a lower reported asthma prevalence than insured children (due to less screening and detection), and that this disparity would be seen primarily in children with intermittent rather than persistent symptoms (because children with persistent symptoms would be more likely to be detected regardless of health insurance status). Additionally, we hypothesized that differences in acute care utilization would be modest, given the tendency of greater screening to detect intermittent rather than persistent asthma.
We used NHANES, a population-based survey of U.S. households conducted by the National Center for Health Statistics. NHANES uses a complex, multistage probability sample of the U.S. civilian, non-institutionalized population. We used the following questionnaire components: 1) Respiratory Health and Disease, 2) Medical Conditions, 3) Hospital Utilization and Access to Care, 4) Prescription Medications, and 5) Demographics. Data from surveys in 2003–2004, 2005–2006, and 2007–2008 were aggregated for our analysis. For children <16, data are reported by an adult in the household, usually a parent or guardian. Our analysis is restricted to 11,719 children ages 1–17.
We used NHANES to assess asthma diagnosis, symptoms, inhaled corticosteroid use, and asthma exacerbation-related acute care visits (at a doctor’s office or ED).
Participants were asked whether a doctor or other health professional had ever told them that they have asthma and, if so, whether they still had the diagnosis. Only participants who answered yes to both questions were considered to have a current diagnosis of asthma, henceforth referred to simply as “diagnosis” of asthma.
The National Heart, Lung, and Blood Institute (NHLBI) Asthma Guidelines (
NHANES does not include all of this information on asthma impairment and risk. Therefore, we used only the NHANES respiratory symptoms questions that matched reasonably well with NHLBI criteria (see
Participants were asked the names of prescribed medications taken in the past 30 days. We considered only the following asthma-related medication categories: 1) inhaled corticosteroids (alone or in combination with long-acting bronchodilators), 2) short-acting bronchodilators, and 3) other long-term control medications, including long-acting bronchodilators (without corticosteroids), leukotriene inhibitors, and mast cell stabilizers. Each medication category was coded as 1 if the child reported taking the medication in the past 30 days. Participants also provided the number of times in the past 12 months they visited a doctor’s office or ED for an “attack of wheezing or whistling.”
We used the following NHANES demographic data: child age, child gender, child race/ethnicity (Hispanic, non-Hispanic White, non-Hispanic Black, and other), child insurance status (insured versus uninsured), and family income as a percentage of the family composition-adjusted federal poverty level. Insurance status was initially categorized as uninsured, publicly-insured (Medicaid and SCHIP), privately-insured, and other. Because differences between (1) uninsured and publicly-insured and (2) uninsured and privately-insured were both significant in the same direction for our main outcome, and because previous literature has documented that publicly- and privately-insured children often receive similar quality of primary care (with publicly-insured children receiving even higher quality care in some cases) (
All analyses used survey-specific weights to account for potential non-response bias and non-coverage of households without a telephone, and to provide national estimates. Analyses were conducted using Stata/SE version 11 (StataCorp LP, College Station, TX) to adjust for the complex survey design. To account for potential bias caused by item non-response, we used imputation by chained equations (
Using logistic regression, we estimated the odds of having a diagnosis of asthma by insurance status, with interaction terms between insurance status and each level of symptom impairment (no symptoms, intermittent asthma symptoms, persistent asthma symptoms). Using logistic regression and controlling for demographic variables, we examined whether insured children, regardless of asthma diagnosis, had higher odds of reporting any, intermittent, or persistent asthma symptoms.
NHLBI classification of severity as determined by symptom impairment and risk only applies to children not currently taking long-term control mediations. For children on long-term control medications, lack of symptom impairment might simply reflect adequacy of control. Since this information was not available through NHANES, we conducted sensitivity analyses to determine whether our multivariate logistic regression results would be altered by limiting our analyses to children not currently on control medications.
Next, we used logistic regression to examine the odds of children with and without insurance a) having used an inhaled corticosteroid in the past 30 days, and b) having a doctor’s office or ED visit in the past 12 months for an asthma attack. In these multivariate regression models, we included demographic variables as covariates. We also conducted additional sensitivity analyses to examine whether any difference detected in the odds of having an asthma exacerbation-related acute visit would be affected by the inclusion of controller asthma medication use in our model.
Among children with a diagnosis of asthma (10%; n=1214), 6% (n=104) were uninsured, and 94% (n=1110) were insured. Forty-nine percent (n=721) of children with asthma symptoms (intermittent or persistent) did not have a diagnosis of asthma. Among all symptomatic but undiagnosed children, 11% were uninsured (
In multivariate regressions controlling for demographics, the odds of having a diagnosis of asthma were 2.08 times greater for insured versus uninsured children (95% CI 1.47–2.94). When interactions between insurance and asthma impairment were included, however, the association held true only for children with no or intermittent symptoms (
In a sensitivity analysis (not shown), we repeated these multivariate regressions using only children who were currently not taking any long-term asthma control medications (NHLBI severity classifications only apply to children not taking long-term control medications). Our results were similar to the analysis with the full sample of children; insured children were more likely to have a diagnosis of asthma (AOR 1.88, 95% CI 1.29, 2.73), and this association was also true for insured children with no (AOR 1.73, 95% CI 1.03–2.90) and intermittent symptoms (AOR 3.49, 95% CI 1.31–9.30), but not for children with persistent symptoms (AOR 1.40, 95% CI 0.80–2.44).
The fact that insured children were more likely to be diagnosed with asthma than uninsured children could not be attributed to a greater reported prevalence of asthma symptoms. In multivariate regressions controlling for both demographics and asthma medication use (not shown), insured children were no more likely to report any (OR 1.05, 95% CI 0.75–1.46), intermittent (OR 0.88, 95% CI 0.54–1.44), or persistent (OR 1.23, 95% CI 0.89–1.70) asthma symptoms than uninsured children.
In multivariate regressions controlling for demographics (
In multivariate regressions controlling for demographics (
Insured children with intermittent asthma symptoms have a greater likelihood of being diagnosed with asthma and receiving long-term inhaled corticosteroid treatment than those without insurance. Further, insured children with intermittent symptoms are also more likely to make acute outpatient and ED visits for asthma attacks. These differences in asthma diagnosis, treatment, and utilization by health insurance were not observed for those with persistent symptoms.
Our findings suggest that, although health insurance may be an important factor in asthma diagnosis among children with intermittent symptoms, it may play a much smaller role in asthma diagnosis among children with persistent symptoms. Insured children with persistent symptoms are about as likely to have a diagnosis of asthma as uninsured children with similar symptoms. One likely explanation is that, because children with persistent symptoms have a higher level of need for acute asthma care, they tend to present to clinics, urgent care centers, and EDs regardless of their insurance status, thus creating similar opportunities for diagnosis.
Among children with intermittent asthma symptoms, insured children were more likely than uninsured children not only to take an inhaled corticosteroid, but also to have had a recent acute care visit or ED visit for “wheezing attacks.” This finding is somewhat counterintuitive, given that inhaled corticosteroids have been shown to reduce acute care utilization. There are at least three plausible explanations for this observation. First, some uninsured children may have a similar need for acute care as insured children but may be unable to receive it consistently because they do not have insurance (
Our findings suggest that there may be a significant “reservoir” of undiagnosed asthmatic children, especially among those who lack health insurance. The benefits of identifying these children, however, are unclear—they are more likely to have intermittent symptoms, which may not benefit greatly from control therapy. As access to insurance expands through health care reform, asthma diagnoses may increase from their current plateau, and we may see additional increases in inhaled corticosteroid use. Such increases, however, may incur a cost that might not greatly improve societal health.
This study has several important limitations. First, based on the age of the participant (1–15 years versus 16–17 years), the data were collected via parent-report or self-report. We do not have data on differences in the accuracy of the reporting methods based on these age groups for reporting asthma-related symptoms, medication, and utilization. Second, our findings are based on cross-sectional data, and we are unable to determine the temporal ordering of events. For example, some children with no or intermittent symptoms were taking inhaled corticosteroids, and possibly had persistent asthma that was now well-controlled on inhaled corticosteroids. However, our sensitivity analysis suggested that our findings were similar when restricted to children not currently on a control medication. Next, our analysis used a limited number of covariates that could have missed important confounders. For example, our study confirms previous studies showing that asthma diagnosis and symptoms vary by race/ethnicity (
In conclusion, we found that having health insurance is associated with an increased likelihood that a child with intermittent asthma symptoms will receive an asthma diagnosis and asthma control medication, but is not associated with improvements in asthma-related acute care utilization. We also found that, for children with persistent symptoms, having health insurance is not associated with diagnosis, treatment, or utilization. These findings suggest that while increasing access to insurance could lead to the identification of more children with intermittent asthma symptoms, benefits with respect to acute care utilization remain unclear. CHIPRA and expanded Medicaid coverage of parents under the ACA may lead to many previously uninsured children in the U.S. becoming insured (
Supported by Grant U48 DP000056-04 from the Centers for Disease Control and Grant RC2HL101811-01 from the National Heart, Lung, and Blood Institute, National Institutes of Health. Dr. Kaplan is currently employed by the NIH.
The authors have no other conflicts of interest or corporate sponsors to report.
No other disclosures.
Sample Characteristics (
| General Characteristics | % | N |
|---|---|---|
| Child Gender- Female | 49 | 5803 |
| Child Race/Ethnicity | ||
| Hispanic | 19 | 4258 |
| Non-Latino Black | 15 | 3505 |
| Non-Hispanic Other | 7 | 621 |
| Non-Hispanic White | 59 | 3330 |
| Child Age | ||
| <5 years | 24 | 3271 |
| 5–11 | 40 | 4074 |
| 12–18 | 37 | 4369 |
| Income as % FPL | ||
| 0–99% | 22 | 3798 |
| 100–199% | 23 | 3137 |
| 200–399% | 30 | 2990 |
| ≥400% | 25 | 1789 |
| Health Insurance | ||
| Uninsured | 11 | 1670 |
| Private | 56 | 4945 |
| Medicaid/SCHIP | 22 | 3525 |
| Other (Military, Indian Health Service, other | 10 | 1502 |
| Survey Year | ||
| 2003–2004 | 33 | 4022 |
| 2005–2006 | 33 | 4256 |
| 2007–2008 | 33 | 3436 |
| Has a current diagnosis of asthma | 10 | 1214 |
| Wheeze in past year | 13 | 1540 |
| Sleep disturbance | ||
| Never | 93 | 10803 |
| <1/week | 4 | 480 |
| At least 1/week | 3 | 431 |
| Activity Limitation, any | 6 | 679 |
| Currently taking ICS | 2 | 290 |
| Currently taking other long-term controller medication | 3 | 245 |
| Currently taking short-acting bronchodilator | 5 | 577 |
| Asthma Symptom Severity | ||
| No symptoms | 87 | 10174 |
| Intermittent symptoms | 5 | 562 |
| Persistent symptoms | 8 | 978 |
includes long acting bronchodilators and immunomodulators
Child Insurance Status by Asthma Diagnosis
| Insured, % (n) | Uninsured, % (n) | |
|---|---|---|
| Current asthma diagnosis | 94 (1110) | 6 (104) |
| Undiagnosed, symptomatic | 89 (647) | 11 (74) |
| Undiagnosed, asymptomatic | 88 (8287) | 12 (1492) |
Adjusted odds ratio of having a current asthma diagnosis by insurance status and disease impairment.
| Predictor | Unadjusted Odds Ratio (95% CI) | Adjusted Odds Ratio (95% CI) |
|---|---|---|
| Insured (Uninsured at each of 3 symptoms levels is reference category) | ||
| With no asthma symptoms | 1.91 (1.16–3.14) | 2.01 (1.23–3.31) |
| With intermittent asthma symptoms | 3.57 (1.34–9.51) | 4.08 (1.57–10.61) |
| With persistent asthma symptoms | 1.39 (0.81–2.40) | 1.45 (0.88–2.39) |
| Household Income as % of FPL | ||
| 0–99% | Reference | Reference |
| 100–199% | 0.86 (0.65–1.14) | 0.77 (0.54–1.09) |
| 200–399% | 0.90 (0.67–1.20) | 0.83 (0.58–1.19) |
| ≥400% | 0.84 (0.66–1.06) | 0.77 (0.54–1.08) |
| Race/Ethnicity | ||
| White non-Hispanic | Reference | Reference |
| Hispanic | 0.85 (0.72–1.02) | 1.03 (0.79–1.35) |
| Black non-Hispanic | 1.70 (1.44–2.01) | 1.84 (1.49–2.27) |
| Other | 0.81 (0.51–1.30) | 1.01 (0.62–1.64) |
| Child age (years) | 1.04 (1.03–1.06) | 1.11 (1.09–1.12) |
| Child gender- female | 0.86 (0.73–1.01) | 0.98 (0.81–1.18) |
| Survey wave | ||
| 2003–04 | Reference | Reference |
| 2005–06 | 1.20 (1.01–1.42) | 1.29 (1.02–1.63) |
| 2007–08 | 1.14 (0.96–1.37) | 1.28 (0.96–1.69) |
Adjusted odds ratio of using inhaled corticosteroids (past 30 days) by insurance status and disease impairment.
| Predictor | Unadjusted Odds Ratio (95% CI) | Adjusted Odds Ratio (95% CI) |
|---|---|---|
| Insured (Uninsured at each of 3 symptoms levels is reference category) | ||
| With no asthma symptoms | 11.21 (2.36–53.19) | 10.54 (2.24–49.71) |
| With intermittent asthma symptoms | 4.96 (1.36–18.08) | 4.51 (1.18–17.24) |
| With persistent asthma symptoms | 1.21 (0.55–2.64) | 1.18 (0.53–2.61) |
| Household Income as % of FPL | ||
| 0–99% | Reference | Reference |
| 100–199% | 0.83 (0.50–1.38) | 0.79 (0.46–1.35) |
| 200–399% | 0.83 (0.55–1.26) | 0.79 (0.50–1.27) |
| ≥400% | 1.09 (0.70–1.70) | 1.07 (0.65–1.78) |
| Race/Ethnicity | ||
| White non-Hispanic | Reference | Reference |
| Hispanic | 0.73 (0.51–1.04) | 0.88 (0.60–1.29) |
| Black non-Hispanic | 1.39 (1.03–1.87) | 1.27 (0.94–1.72) |
| Other | 0.51 (0.21–1.24) | 0.58 (0.25–1.36) |
| Child age (years) | 1.00 (0.97–1.03) | 1.03 (0.99–1.06) |
| Child gender- female | 0.79 (0.56–1.10) | 0.91 (0.64–1.30) |
| Survey wave | ||
| 2003–04 | Reference | Reference |
| 2005–06 | 1.85 (1.34–2.56) | 1.90 (1.39–2.59) |
| 2007–08 | 1.84 (1.28–2.65) | 1.99 (1.33–2.98) |
Adjusted odds ratio of having a doctor’s visit or emergency department visit for an asthma attack (past 12 months) by insurance status and disease impairment.
| Predictor | Unadjusted Odds Ratio (95% CI) | Adjusted Odds Ratio (95% CI) |
|---|---|---|
| Insured (Uninsured at each of 3 symptoms levels is reference category) | ||
| With no asthma symptoms | 1.87 (0.23–14.97) | 2.20 (0.28–17.36) |
| With intermittent asthma symptoms | 5.26 (1.17–23.65) | 5.21 (1.21–22.53) |
| With persistent asthma symptoms | 0.95 (0.41–2.21) | 1.03 (0.42–2.52) |
| Household Income as % of FPL | ||
| 0–99% | Reference | Reference |
| 100–199% | 0.91 (0.62–1.33) | 0.93 (0.62–1.39) |
| 200–399% | 0.52 (0.34–0.79) | 0.57 (0.36–0.91) |
| ≥400% | 0.52 (0.31–0.89) | 0.68 (0.39–1.19) |
| Race/Ethnicity | ||
| White non-Hispanic | Reference | Reference |
| Hispanic | 1.30 (0.83–2.02) | 1.43 (0.86–2.38) |
| Black non-Hispanic | 2.77 (1.92–3.98) | 2.44 (1.65–3.59) |
| Other | 0.99 (0.45–2.16) | 1.27 (0.54–3.01) |
| Child age (years) | 0.97 (0.94–1.00) | 1.02 (0.98–1.05) |
| Child gender- female | 0.59 (0.40–0.88) | 0.74 (0.48–1.13) |
| Survey wave | ||
| 2003–04 | Reference | Reference |
| 2005–06 | 1.11 (0.73–1.69) | 1.15 (0.79–1.68) |
| 2007–08 | 0.94 (0.61–1.46) | 0.98 (0.61–1.57) |