Long-Term Ambient Air Pollution and Childhood Eczema in the United States.

Introduction

Growing epidemiological evidence suggests that ambient air pollution, including fine particulate matter [PM in aerodynamic diameter ()], ozone (), and nitrogen dioxide (), may have detrimental effects on skin and may precipitate or exacerbate eczema, particularly during the perinatal and early childhood periods, as summarized in a review by Hassoun et al.[1] This effect is potentially due to direct oxidative stress on the skin.[1] Studies among children in Europe and Asia have demonstrated that increased exposure to outdoor air pollution is associated with increased prevalence of and visits for eczema in some populations[2,3] but not in others.[4] In North America, an early life cohort in Toronto, Ontario, Canada, found associations between eczema and concentrations.[5] Although analyses of eczema and pollution aggregated by state have been performed in the United States,[6] to our knowledge there have not been analyses with substate exposure assessment performed to understand the impact of air pollution on eczema in a national sample of children.

Methods

We used the Medicaid Analytic eXtract (MAX) from 2009–2010, which includes Medicaid eligibility, demographic information, ZIP code tabulation area (ZCTA) of residence, and utilization records. We included individuals from birth through 18 years of age who were eligible for Medicaid from their 2009 birthday through their 2010 birthday. We defined eczema diagnosis according to the International Classification of Diseases, Ninth Revision, Clinical Modification (ICD-9-CM code 691.8)[7] for any visit during the study period. We assigned exposures of long-term (2009–2010) average and and warm-season (May–September) average using a set of publicly available air pollution concentration predictions from the Center for Air, Climate, and Energy Solutions (CACES).[8] Exposure predictions were aggregated to ZCTA averages from a census tract resolution.

Because of data quality issues of incomplete utilization data, low average months of eligibility (), and incomplete data on self-reported race/ethnicity [categorized as Asian, Black, Hispanic, White, Grouped, Unknown; “Grouped” combined Native American/Alaskan, Hawaiian, race (Hispanic), race (non-Hispanic) due to small numbers], we excluded data from Arkansas, Colorado, Idaho, Iowa, Kansas, Maine, Massachusetts, Ohio, Pennsylvania, Rhode Island, Vermont, Washington, and West Virginia. In addition, we excluded Alaska and Hawaii because of the absence of exposure predictions. Use of the data and waiver of informed consent was approved by the Johns Hopkins School of Medicine institutional review board.

We estimated odds ratios for eczema diagnosis using generalized estimating equations with logit link and allowing for clustering by ZCTA, separately by age groups. We fit a multipollutant model with , , and , as well as single-pollutant models. Models were adjusted for sex, self-reported race/ethnicity (due to associations with air pollution and with eczema rates[9]), ZCTA-level household poverty rates, season of birth,[9] state (due to differences in Medicaid procedures by state), and unmeasured spatial confounding using 15 degrees of freedom spatial splines.[10]

Results

Of the 16,089,050 children included, 51% were male, 34% White, 30% Hispanic, 27% Black, and 2% Asian (Table 1). The overall prevalence of eczema was 2.7%: highest among those in the first year of life (7.1%) and decreasing with age to 0.8% among those 16–18 years. During the study period, the median [minimum, quartile 1 (Q1), Q3, maximum] of ZCTA-average pollution levels were (2.4, 7.0, 9.8, 16.1) for , (26.2, 41.8, 47.3, 58.4) for , and (0.6, 3.1, 5.9, 31.2) for .

Table 1

Characteristics of Medicaid extract population by eczema status.

Characteristica	Overall	Eczema	No eczema
Total sample (n)	16,089,050	432,774	15,656,276
Sex [n (%)]
Female	7,865,322 (48.9)	222,361 (51.4)	7,642,961 (48.8)
Male	8,223,728 (51.1)	210,413 (48.6)	8,013,315 (51.2)
Self-reported race/ethnicity [n (%)]
Asian	349,974 (2.3)	14,568 (3.4)	360,406 (2.3)
Black	4,306,462 (26.8)	151,924 (35.1)	4,154,538 (26.5)
Groupedb	409,783 (2.5)	8,779 (2.0)	401,004 (2.6)
Hispanic	4,803,579 (29.9)	125,175 (28.9)	4,678,404 (29.9)
White	5,451,305 (33.9)	108,955 (25.2)	5,342,350 (34.1)
Unknown	742,947 (4.6)	23,373 (5.4)	719,574 (4.6)
Age (y), [n (%)]
<1	1,310,819 (8.1)	93,689 (21.6)	1,217,130 (7.8)
1–3	3,385,990 (21.0)	149,483 (34.5)	3,236,507 (20.7)
4–6	2,916,389 (18.1)	74,960 (18.1)	2,841,429 (18.1)
7–9	2,490,241 (15.5)	47,602 (11.0)	2,442,639 (15.6)
10–12	2,205,342 (13.7)	31,832 (7.4)	2,173,510 (13.9)
13–15	1,996,687 (12.4)	20,995 (4.9)	1,975,692 (12.6)
16–18	1,783,582 (11.1)	14,213 (3.3)	1,769,369 (11.3)
ZCTA-level poverty (%), [n (%)]
≤5	1,512,968 (9.4)	37,880 (8.8)	1,475,088 (9.4)
6–10	3,399,517 (21.1)	87,359 (20.2)	3,312,158 (21.2)
11–15	3,691,127 (22.9)	100,988 (23.3)	3,590,139 (22.9)
16–20	2,849,931 (17.7)	76,502 (17.7)	2,773,429 (17.7)
21–25	1,818,998 (11.3)	51,449 (11.9)	1,767,549 (11.3)
26–100	2,816,509 (17.5)	78,596 (18.2)	2,737,913 (17.5)

Note: Population includes individuals eligible for Medicaid from their birthday in 2009 to their birthday in 2010. ZCTA, ZIP code tabulation area.

No missing values.

Grouped race/ethnicity is the combination of “Native American/Alaskan,” “ race (Hispanic),” “ race (non-Hispanic),” and “Hawaiian.”

Odds of incident eczema during the first year of life were 2.8% higher (95% confidence interval: 1.021, 1.034) for each higher long-term concentration, when adjusting for and (Table 2). The associations between eczema prevalence and were similar in older age groups. There was some evidence of an association between eczema and in the youngest age groups, but this did not hold across all ages. In single-pollutant models, was associated with eczema diagnosis, but this did not persist when adjusting for and .

Table 2

Estimated odds ratios (95% confidence intervals) between a 1-unit difference in long-term ambient air pollution and eczema incidence (first year of life) or prevalence (all other ages), in the Medicaid population, 2009–2010, from a generalized estimating equations model.

Age (y)/model	PM_2.5 (per 1μg/m^3)	O_3 (per 1 ppb)	NO_2 (per 1 ppb)
<1
Unadjusted single-pollutant	1.052 (1.044, 1.061)	0.996 (0.993, 0.999)	1.006 (1.001, 1.010)
Adjusted single-pollutanta	1.049 (1.036, 1.061)	1.004 (0.996, 1.012)	1.024 (1.019, 1.028)
Adjusted multipollutantb	0.987 (0.970, 1.003)	1.010 (1.003, 1.019)	1.028 (1.021, 1.034)
1–3
Unadjusted single-pollutant	1.020 (1.012, 1.028)	0.995 (0.992, 0.998)	0.995 (0.992, 0.997)
Adjusted single-pollutanta	1.050 (1.040, 1.060)	1.003 (0.997, 1.010)	1.020 (1.017, 1.024)
Adjusted multipollutantb	1.006 (0.993, 1.020)	1.010 (1.004, 1.017)	1.020 (1.014, 1.025)
4–6
Unadjusted single-pollutant	1.034 (1.025, 1.044)	0.994 (0.991, 0.997)	1.003 (1.000, 1.006)
Adjusted single-pollutanta	1.071 (1.059, 1.083)	0.995 (0.987, 1.003)	1.028 (1.024, 1.032)
Adjusted multipollutantb	1.012 (0.994, 1.029)	1.005 (0.997, 1.013)	1.026 (1.020, 1.032)
7–9
Unadjusted single-pollutant	1.037 (1.028, 1.046)	0.994 (0.991, 0.998)	1.008 (1.005, 1.011)
Adjusted single-pollutanta	1.063 (1.050, 1.077)	0.987 (0.979, 0.996)	1.028 (1.024, 1.033)
Adjusted multipollutantb	0.999 (0.981, 1.017)	0.999 (0.991, 1.007)	1.028 (1.022, 1.035)
10–12
Unadjusted single-pollutant	1.038 (1.029, 1.048)	0.996 (0.992, 1.000)	1.008 (1.005, 1.011)
Adjusted single-pollutanta	1.074 (1.069, 1.089)	0.989 (0.980, 0.999)	1.028 (1.023, 1.033)
Adjusted multipollutantb	1.021 (1.001, 1.042)	1.000 (0.990, 1.010)	1.023 (1.016, 1.030)
13–15
Unadjusted single-pollutant	1.039 (1.029, 1.049)	1.000 (0.997, 1.004)	1.008 (1.005, 1.011)
Adjusted single-pollutanta	1.072 (1.056, 1.089)	0.985 (0.975, 0.995)	1.028 (1.023, 1.034)
Adjusted multipollutantb	1.017 (0.995, 1.040)	0.997 (0.986, 1.007)	1.024 (1.016, 1.032)
16–18
Unadjusted single-pollutant	1.028 (1.018, 1.039)	1.001 (0.997, 1.006)	1.007 (1.004, 1.010)
Adjusted single-pollutanta	1.038 (1.020, 1.057)	0.982 (0.970, 0.993)	1.021 (1.015, 1.027)
Adjusted multipollutantb	0.985 (0.960, 1.011)	0.992 (0.980, 1.005)	1.024 (1.014, 1.033)

Note: , ozone; , nitrogen dioxide; , fine particulate matter; ZCTA, ZIP code tabulation area.

Adjusted single-pollutant models included sex (male, female), self-reported race/ethnicity [Asian, Black, Hispanic, White, Grouped, Unknown; “Grouped” combined Native American/Alaskan, Hawaiian, race (Hispanic), race (non-Hispanic)], ZCTA-level household poverty rates (, 6–10%, 11–15%, 16–20%, 21–25%, 25–100%), season of birth (December–February, March–May, June–August, September–November), state, and unmeasured spatial confounding using 15 degrees of freedom spatial splines.

Adjusted multipollutant models included all variables from single-pollutant models and , , and .

Discussion

In a large, geographically and racially diverse population of children, we demonstrated that long-term ambient concentrations were associated with eczema incidence in the first year of life. Eczema, particularly in early life, is known to be associated with increased risk for multiple atopic diseases, including food allergy, asthma, and allergic rhinitis. Thus, exposures that increase eczema risk may also increase risk for other allergic diseases, and exposure reduction may decrease development of multiple allergic diseases.

Limitations of this study include the use of data that was not collected primarily for research purposes. Other uncaptured factors such as health-care seeking behaviors and secondhand smoke exposure could confound the analysis. Ambient pollution exposures were assessed as an area (i.e., ZCTA) average, and thus do not perfectly reflect personal exposures. Future work should also investigate the effects of measurement error on the estimated associations.[11] For newborns, our analysis estimated associations with cumulative incidence of eczema, but for older age groups this approach is limited to associations with prevalent eczema owing to a lack of individual health-care history information prior to the study period.

In sum, in a very large U.S. cohort, we found that average exposure to was associated with eczema prevalence. Because eczema is so central to the development of other allergic diseases, reducing exposure to may not only prevent development of eczema but also other allergic diseases. Future research is needed to understand longitudinal associations and their mechanisms.