<title>Materials and Methods</title> <p>The data presented here were originally collected for a recent study of humans exposed to low levels of O<sub>3</sub> (##REF##16393927##Adams 2006##). The exposures of interest for the purpose of the analysis presented here are the constant-concentration or S-W exposures to 0.06 ppm O<sub>3</sub> and to FA. For purposes of comparison with other studies, we also present some results from the 0.08-ppm S-W O<sub>3</sub> exposures from the ##REF##16393927##Adams (2006)## study. Although only group statistics were presented in the ##REF##16393927##Adams (2006)## publication, each subject’s FEV<sub>1</sub> measurement before and after the 6.6-hr exposures was made available by the author to the U.S. EPA for inclusion in its Air Quality Criteria Document for O<sub>3</sub> and Related Photochemical Oxidants (##UREF##4##U.S. EPA 2006##) and its health risk assessment (##UREF##5##U.S. EPA 2007##). We analyzed these individual pre- and postexposure FEV<sub>1</sub> data.</p> <p>The question of interest here is whether a 6.6-hr exposure to 0.06 ppm O<sub>3</sub> under the conditions of the ##REF##16393927##Adams (2006)## study results in postexposure FEV<sub>1</sub> decrements greater than those after a control exposure to FA. We calculated the FEV<sub>1</sub> percent decrement for FA and for 0.06-ppm O<sub>3</sub> exposures for each of the 30 participants as 100% × (preexposure FEV<sub>1</sub> – postexposure FEV<sub>1</sub>)/preexposure FEV<sub>1</sub>. We then calculated the FEV<sub>1</sub> response due to O<sub>3</sub> (i.e., O<sub>3</sub>-induced) by subtracting the percent decrement after FA from the percent decrement after 0.06 ppm O<sub>3</sub> for each volunteer. The distribution of O<sub>3</sub>-induced responses in these data did not appear to deviate markedly from a Gaussian distribution. However, it is well known that higher-dose O<sub>3</sub> exposures that produce larger group mean FEV<sub>1</sub> responses result in frequency distributions of response that are quite skewed, thereby potentially challenging some of the assumptions of many parametric statistical tests (##REF##4014870##Kulle et al. 1985##; ##REF##21781722##McDonnell 1996##; ##REF##7812569##Weinmann et al. 1995##). The nonparametric sign test, which assumes only that the responses of each subject are independent and makes no assumptions about the distribution of the response data, is appropriate to test the null hypothesis that observed values have the same probability of being positive or negative (##UREF##0##Fisher and Belle 1993##). We therefore selected the sign test as our primary test of the null hypothesis that the FEV<sub>1</sub> responses for the FA and 0.06-ppm exposures are not different.</p> <p>Because the individual O<sub>3</sub>-induced decrements in this study were generally symmetrical and because other studies have demonstrated that exposures that produce mean responses of the magnitude observed in this study result in roughly symmetric response distributions (##REF##4014870##Kulle et al. 1985##; ##UREF##1##McDonnell et al. 1983##), we also compared the FA and 0.06-ppm O<sub>3</sub> responses using other methods. We used the Wilcoxon signed rank test, which makes the assumption that the individual O<sub>3</sub>-induced responses are symmetrically distributed, and the paired <italic>t</italic>-test, which makes the further assumption that the responses are normally distributed (##UREF##0##Fisher and Belle 1993##).</p> <p>We calculated two-sided statistical tests using SYSTAT 5.0 (Systat, Inc., Evanston, IL), and we examined Tukey box plots to assess potential outlier data using Graph Pad Prism 5 (Graph Pad Software, Inc., San Diego, CA).</p>
<title>Results</title> <p>##TAB##0##Table 1## lists the individual percentage decrements in FEV<sub>1</sub> from baseline after the FA and 0.06-ppm O<sub>3</sub> exposures and the O<sub>3</sub>-induced decrements. For the full data set (<italic>n</italic> = 30), the O<sub>3</sub>-induced FEV<sub>1</sub> responses appear to be symmetrically distributed around the median of 2.91% and mean of 2.85%. Twenty-four of the 30 individuals experienced an O<sub>3</sub>-induced decrement greater than zero (range, 0.23–14.52%), whereas six experienced an improvement in FEV<sub>1</sub> (range, −0.43% to −7.42%) after the exposure. The null hypothesis that there is no difference between the median responses of the FA and the 0.06-ppm exposures (or that the median O<sub>3</sub>-induced decrement equals zero) is rejected using the two-tailed sign test (<italic>p</italic> = 0.0019). We also conducted alternative analyses of the data using the Wilcoxon signed rank test and the paired <italic>t</italic>-test. The null hypothesis of no difference between responses for the FA and 0.06-ppm O<sub>3</sub> exposures was rejected by both tests (##TAB##1##Table 2##). Although the data had no extreme outliers, we flagged three responses as potential outliers according to the Tukey criteria. The characteristics of the data change little with exclusion of the single most extreme value (subject 23 in ##TAB##0##Table 1##) or all three potential outliers (subjects 10, 12, and 23 in ##TAB##0##Table 1##) removed (##TAB##1##Table 2##).</p>
<title>Discussion</title> <p>We have demonstrated that the FEV<sub>1</sub> decrements that occur after a 6.6-hr exposure to 0.06 ppm O<sub>3</sub> are statistically different from those that occur after FA exposure (<italic>p</italic> &lt; 0.01). We arrive at the same finding regardless of the statistical test we employ or the approach to treating potential outliers in the data. That the effect of 0.06 ppm O<sub>3</sub> on FEV<sub>1</sub> occurred not by chance alone is further supported by two additional observations. First, the FA and 0.06-ppm responses in FEV<sub>1</sub> generally track each other for the first 4.6 hr of exposure, with no evidence of wide swings in the data. The responses clearly diverge for both the 5.6- and 6.6-hr data points, indicating that the response at 6.6 hr is not a single anomalous data point (##FIG##0##Figure 1##). The group mean O<sub>3</sub>-induced decrement at 5.6 hr (~ 2.4%) is only marginally smaller than that at 6.6 hr (2.85%). This temporal pattern of response is generally consistent with patterns of response after 0.08 ppm, 0.10 ppm, and 0.12 ppm in numerous studies in which the O<sub>3</sub> response begins to diverge from the FA response at earlier time points during exposure to higher concentrations of O<sub>3</sub> (##REF##10910115##Adams 2000##, ##REF##12122573##2002##, ##REF##12579457##2003##; ##REF##3356996##Folinsbee et al. 1988##; ##REF##2240838##Horstman et al. 1990##). Second, the magnitude of the group mean O<sub>3</sub>-induced response of this sample after exposure to 0.08 ppm O<sub>3</sub> is 6.07%, which is quite consistent with observed responses to 0.08-ppm exposure from other studies (##FIG##1##Figure 2##), indicating that this sample of volunteers is not unusually sensitive to O<sub>3</sub>. We thus have no reason to suspect that the observed average response at 0.06 ppm is inflated because of attributes of the target population or sampling error.</p> <p>The existence of a small group mean FEV<sub>1</sub> decrement after a 6.6-hr exposure of young exercising adults to 0.06 ppm should not come as a surprise. ##FIG##1##Figure 2## presents response data from studies that used an exposure protocol nearly identical to that used by ##REF##16393927##Adams (2006)##. These studies all used young, healthy adults as volunteers; exposure duration was for 6.6 hr, and exercise pattern and V<sub>E</sub> (~20 L/min/m<sup>2</sup> BSA) were similar. The group mean FEV<sub>1</sub> response to the 0.08-ppm exposure for the ##REF##16393927##Adams (2006)## study is consistent with other studies. Furthermore, the observed FEV<sub>1</sub> responses at 0.04 ppm O<sub>3</sub> (##REF##12122573##Adams 2002##) and 0.06 ppm O<sub>3</sub> (##REF##16393927##Adams 2006##) are almost identical to the response predicted by a model based on data from 15 studies conducted at the U.S. EPA Human Studies Facility in Chapel Hill, North Carolina (##REF##17497527##McDonnell et al. 2007##). The smooth C–R curve illustrated in ##FIG##1##Figure 2## is consistent with C–R curves for shorter-duration (2 hr) exposures, which have typically been observed to be smooth without obvious discontinuities over a wide range of concentrations, including those where effects were near zero (##REF##6481003##Avol et al. 1984##; ##REF##3298195##Hazucha 1987##; ##REF##4014870##Kulle et al. 1985##; ##UREF##1##McDonnell et al. 1983##).</p> <p>The stark difference between our conclusions and those of ##REF##16393927##Adams (2006)## with regard to whether a 6.6-hr exposure to 0.06 ppm O<sub>3</sub> induces statistically significant FEV<sub>1</sub> decrements requires further explanation. We have identified three factors that we believe contribute to the difference in conclusions. First, no <italic>p</italic>-value is given in the original manuscript for the comparison of the 6.6-hr FA and 0.06-ppm responses. The group mean difference of 2.85% is simply reported as not being statistically significantly different from zero at α = 0.05 using the Scheffé test to correct for the multiple comparisons. However, in Table 3 of the original manuscript, the difference between the 0.08-ppm and 0.06-ppm exposures after 6.6 hr (3.21%) is reported as being statistically different from zero. Because the analysis of variance and the Scheffé method used by Adams assume equal variances for all means, it is reasonable to assume that the difference of 2.85% between 0.06 ppm and FA approached statistical significance—even with this most conservative methodology.</p> <p>A second factor causing differences in conclusions reached herein compared with those of ##REF##16393927##Adams (2006)## results from differences in the purpose of our reanalysis compared with the purpose of the original study, the statistical approaches used, and the approach to controlling for multiple statistical tests. The stated purpose of the ##REF##16393927##Adams (2006)## study implies a large number of comparisons among six exposure protocols and seven time points (0, 1, 2, 3, 4.6, 5.6, and 6.6 hr). The Scheffé method allows all pairwise comparisons as well as an infinite number of linear contrasts among the cell means to be made while limiting the probability of making a single type 1 statistical error among all the potential contrasts to 0.05. Although there is nothing inherently wrong with making a large number of contrasts and strictly maintaining a studywide alpha level using the Scheffé method, this approach comes at the cost of reduced statistical power for assessing differences for specific comparisons. Setting aside all the theoretically possible linear contrasts, there are 15 possible direct comparisons between the six protocols used by ##REF##16393927##Adams (2006)## at the 6.6-hr time point. The Bonferroni procedure would be the preferred multiple comparison correction for this relatively small number of comparisons (##UREF##3##Schwertman and Carter 1995##). A critical alpha for the possible comparisons between the six protocols at the 6.6-hr time point would be 0.05 ÷ 15, or 0.0033. We compared only the FEV<sub>1</sub> responses at 6.6 hr between FA and 0.06-ppm O<sub>3</sub> S-W exposure. Even with a correction for the additional comparisons, which we did not consider, all of the tests presented in ##TAB##1##Table 2## remain statistically significant.</p> <p>The third factor potentially contributing to the disparity in our conclusions compared with those of ##REF##16393927##Adams (2006)## involves errors caused by data not meeting the criteria for the statistical tests applied. The two-factor analysis of variance and Scheffé method cited by ##REF##16393927##Adams (2006)## assume that data are normally distributed and that variances are equal within cells. From previous studies of higher O<sub>3</sub> exposures, we know that FEV<sub>1</sub> responses become skewed and that variance increases (##REF##21781722##McDonnell 1996##). This increase in variance is clearly apparent in the ##REF##16393927##Adams (2006)## data, with the standard deviation of FEV<sub>1</sub> responses increasing from 2.98% for FA to 4.24% for 0.06 ppm O<sub>3</sub> to 8.65% at 0.08 ppm. It is possible that the wide range in variances among the cells resulted in wider confidence levels and inaccuracies of the reported <italic>p</italic>-values for a subset of the comparisons.</p> <p>Assuming for the moment that the O<sub>3</sub>-induced decrement at 0.06 ppm is not zero and that the best point estimate of the magnitude of the mean decrement is 2.85% (95% confidence interval, 1.26–4.45%), what can we say about the possible clinical significance of reversible effects of such magnitude? It is unlikely that individuals experiencing a 3% reduction in FEV<sub>1</sub> would be aware of such an effect, and effects of this magnitude are at the outer range of expected day-to-day variability of the measurement. We know, however, that individuals vary reproducibly in their responses to O<sub>3</sub> exposure, and it is those most responsive individuals who are likely to experience clinically significant effects. Although the average response was small, two subjects in the ##REF##16393927##Adams (2006)## study had &gt; 10% FEV<sub>1</sub> decrements (12.8% and 14.5%). The U.S. EPA has considered any individual changes in FEV<sub>1</sub> of 10–20% to be a moderate effect clearly outside the range of normal within-day variability (##UREF##4##U.S. EPA 2006##, ##UREF##5##2007##). In the ##REF##16393927##Adams (2006)## study, 2 of 30 individuals (i.e., 7%) experienced such effects. This observed proportion of individuals having a &gt; 10% decrement in FEV<sub>1</sub> at 0.06 ppm is consistent with a smooth C–R curve that includes observed proportions from previous studies of 26% at 0.08 ppm, 41% at 0.10, and 57% at 0.12 ppm [proportions calculated for S-W exposures in ##UREF##5##U.S. EPA (2007)##, Table 5–3]. If one converts the SD values to SE values in ##REF##16393927##Adams (2006##, Table 4), the SEs for the symptoms resulting from the 0.06-ppm S-W exposure do not overlap those for the FA exposure. This is suggestive of an effect of 0.06 ppm on respiratory symptoms as well as FEV<sub>1</sub>. A reversible loss of lung function in combination with the presence of symptoms is considered adverse (##REF##10673213##American Thoracic Society 2000##). It thus appears that a small fraction of individuals exposed to 0.06 ppm O<sub>3</sub> for 6.6 hr during moderate exercise may approach a degree of response that is considered to be adverse.</p> <p>To meet the objectives of his study, ##REF##16393927##Adams (2006)## required that a large number of comparisons be made and that comparisons not be identified as statistically significant by chance alone. Appropriately, the Scheffé test was employed to meet these needs. Although ##REF##16393927##Adams (2006)## did not find the FEV<sub>1</sub> responses of the 0.06 ppm O<sub>3</sub> and FA exposures to be statistically different, no measure of the probability of a type 2 statistical error was provided, which would be required before drawing a conclusion that a true difference does not exist. The objective of the present study was to reevaluate the lung function data of subjects exposed for 6.6 hr to 0.06 ppm O<sub>3</sub>. Regardless of the statistical test used, we found the post-exposure FEV<sub>1</sub> decrements for the FA and 0.06-ppm O<sub>3</sub> exposures to be strongly significantly different. Complete resolution of this question must necessarily await further studies designed to address this specific question with adequate statistical power. However, comparison with the results of other studies support the interpretation that our finding is not due to chance alone and, indeed, is consistent with a smooth C–R curve.</p>
<title>Background</title> <p>Ozone is a potent photochemical oxidant that produces transient, reversible decrements in the lung function of acutely exposed individuals. A recent study provided previously unavailable clinical data for 30 healthy young adults exposed to O<sub>3</sub> at 0.06 ppm. That study showed significant effects of 0.08 ppm on lung function, confirming the findings of others. However, exposure to 0.06 ppm O<sub>3</sub> was not reported to significantly affect lung function.</p> <title>Objectives</title> <p>We conducted this analysis to reevaluate the existing lung function data of the volunteers previously exposed to 0.06 ppm O<sub>3</sub>.</p> <title>Methods</title> <p>We obtained pre- and postexposure data on forced expiratory volume in 1 sec (FEV<sub>1</sub>) for all subjects who were previously exposed for 6.6 hr to filtered air or to 0.06 ppm or 0.08 ppm O<sub>3</sub>. We used standard statistical methods appropriate for paired comparisons to reanalyze FEV<sub>1</sub> responses after exposure to 0.06 ppm O<sub>3</sub> relative to filtered air.</p> <title>Results</title> <p>Controlling for filtered air responses, 24 of the 30 subjects experienced an O<sub>3</sub>-induced decrement in FEV<sub>1</sub>. On average, 0.06 ppm O<sub>3</sub> exposure caused a 2.85% reduction in FEV<sub>1</sub> (<italic>p</italic> &lt; 0.002), which was consistent with the predicted FEV<sub>1</sub> response from existing models. Although the average response was small, two subjects had &gt; 10% FEV<sub>1</sub> decrements.</p> <title>Conclusions</title> <p>Exposure to 0.06 ppm O<sub>3</sub> causes a biologically small but highly statistically significant decrease in mean FEV<sub>1</sub> responses of young healthy adults.</p>
<p>Acute exposure to ozone causes transient respiratory symptoms, reversible decrements in pulmonary function, and an inflammatory response that may persist for at least 18–24 hr after exposure. A thorough review of recent epidemiologic and controlled human exposure studies is available elsewhere [##UREF##4##U.S. Environmental Protection Agency (EPA) 2006##]. Controlled exposures of healthy young adults show that the magnitude of these respiratory effects is a function of O<sub>3</sub> concentration, minute ventilation (V<sub>E</sub>), and exposure duration. The primary focus of this article is the effect of short-term controlled O<sub>3</sub> exposures on forced expiratory volume in 1 sec (FEV<sub>1</sub>) as a measure of lung function in healthy young adults. Because small changes in spirometry in healthy young adults may result from exercise, diurnal, or other effects in addition to the effects of O<sub>3</sub> during the course of an exposure, we use the term “O<sub>3</sub>-induced” here to designate effects that we have corrected for such extraneous responses as measured during filtered air (FA) exposures.</p> <p>After prolonged, 6.6-hr exposures to O<sub>3</sub> at concentrations of ≥ 0.08 ppm, young healthy adults develop significant reversible decrements in FEV<sub>1</sub> at a moderate level of exercise (V<sub>E</sub> = 40 L/min). Exposures to 0.04-ppm O<sub>3</sub> result in small, statistically nonsignificant O<sub>3</sub>-induced responses (##REF##12122573##Adams 2002##). Volunteers exposed to 0.08 ppm O<sub>3</sub> experience group mean O<sub>3</sub>-induced FEV<sub>1</sub> decrements that range from 6% to 8% (##REF##12579457##Adams 2003##, ##REF##16393927##2006##; ##REF##2240838##Horstman et al. 1990##; ##REF##2039268##McDonnell et al. 1991##); those exposed to 0.10 ppm have group mean decrements of 8–14% (##REF##2240838##Horstman et al. 1990##; ##REF##2039268##McDonnell et al. 1991##); and those exposed to 0.12 ppm have group mean decrements of 13–16% (##REF##12122573##Adams 2002##; ##REF##3356996##Folinsbee et al. 1988##; ##REF##2240838##Horstman et al. 1990##). The distribution of individual responses becomes skewed with increasing exposure concentration and magnitude of the group mean FEV<sub>1</sub> response (##REF##21781722##McDonnell 1996##). Taken together, these data indicate that FEV<sub>1</sub> responses are clearly affected by 6.6-hr exposures to O<sub>3</sub> concentrations ≥ 0.08 ppm. These data also suggest that smaller, but measurable, responses are likely to occur with 6.6-hr exposure to concentrations somewhat below 0.08 ppm. We are particularly interested in estimating the magnitude of FEV<sub>1</sub> responses to concentrations &lt; 0.08 ppm, with the ultimate goals of better characterizing the concentration–response (C–R) relationship and reducing uncertainty in the assessment of risk at low O<sub>3</sub> concentrations.</p> <p>Until recently, published data have not been available for 6.6-hr exposures to O<sub>3</sub> concentrations between 0.04 and 0.08 ppm. ##REF##16393927##Adams (2006)## provided results for healthy young individuals (15 males, 15 females) randomly exposed for 6.6 hr on six separate occasions to FA, to constant or square-wave (S-W) 0.06 ppm and 0.08 ppm O<sub>3</sub>, and to three variable concentration patterns having mean overall exposure O<sub>3</sub> concentrations of 0.04, 0.06, and 0.08 ppm. The subjects (mean age ~ 23 years) were recruited from the University of California, Davis, and the surrounding community. Measures of FEV<sub>1</sub> were conducted before exposure and after approximately 1, 2, 3, 4.6, 5.6, and 6.6 hr of exposure. Each 6.6-hr exposure was conducted in an exposure chamber and included six 1-hr periods in which participants alternated 50 min of exercise with 10 min of rest. An additional 35-min rest/lunch period in the chamber followed the third hour of exposure. Exercise was calibrated to generate a V<sub>E</sub> of approximately 20 L/min/m<sup>2</sup> body surface area (BSA) for each volunteer. There was a minimum of 4 days between exposures. Additional details related to volunteer characteristics, study design, facilities, measurement methods, exposure characterization, and results are available from ##REF##16393927##Adams (2006)##.</p> <p>The stated purpose of the ##REF##16393927##Adams (2006)## study was to compare the responses to the 0.08-ppm S-W exposure with the responses to the other five exposure conditions. Comparisons of responses among the other five exposure conditions (e.g., the 0.06-ppm S-W exposure with the FA exposure) at various time points were also presented. After the detection of statistically significant effects within the data using a two-way analysis of variance technique, the Scheffé multiple comparison test was used to identify which specific comparisons were significantly different. None of the differences between the FEV<sub>1</sub> responses of exposure to 0.06 ppm O<sub>3</sub> and FA were identified as statistically different from zero. However, ##FIG##0##Figure 1##, which we adapted from ##REF##16393927##Adams (2006)##, shows that the response to 0.06-ppm O<sub>3</sub> exposure diverges over time from the response to FA. Additionally, the lack of overlap of the SE bars at the 6.6-hr time point suggests that the postexposure differences between FA and 0.06 ppm O<sub>3</sub> are not likely to be attributed to chance alone.</p> <p>Although the Scheffé method for detecting specific differences in the context of correcting for all possible contrasts in the data avoids type 1 statistical errors (false positives) at the level of the overall study, it is characterized as having relatively low power for detecting small differences for any single comparison of interest and is recognized as being a conservative test (##UREF##3##Schwertman and Carter 1995##). In the absence of calculations of statistical power or the probability of making a type 2 statistical error for the comparison between the postexposure responses of the FA and 0.06-ppm O<sub>3</sub> exposures, we interpret the reported results of the Adams analysis as being inconclusive regarding the existence of an effect of 0.06-ppm O<sub>3</sub> exposure on FEV<sub>1</sub> response. That is, the inability to reject the null hypothesis of no difference between two conditions is not sufficient to conclude that no such difference exists.</p> <p>Because of the potential regulatory implications of the presence or absence of effects at concentrations below the level of the current National Ambient Air Quality Standard (NAAQS) for O<sub>3</sub> (currently 0.075 ppm) (##UREF##2##NAAQS 2008##), we elected to further examine the responses to 0.06 ppm O<sub>3</sub> documented in the ##REF##16393927##Adams (2006)## study. Because the U.S. EPA risk assessment for lung function effects and the current NAAQS for O<sub>3</sub> are generally based on the postexposure responses of a group of published 6.6-hr S-W studies, we conducted a targeted, secondary analysis of the Adams data to focus on the specific question of whether exposure to 0.06 ppm O<sub>3</sub> for 6.6 hr results in FEV<sub>1</sub> decrements relative to the FA exposure.</p>
<fig id="f1-ehp0116-001023" position="float"><label>Figure 1</label><caption><p>Mean FEV<sub>1</sub> decrements as function of exposure duration and O<sub>3</sub> concentration. Data are for constant, S-W O<sub>3</sub> protocols in the ##REF##16393927##Adams (2006)## study. Error bars are the SE of responses at 6.6 hr. Adapted from ##REF##16393927##Adams (2006)##.</p></caption></fig> <fig id="f2-ehp0116-001023" position="float"><label>Figure 2</label><caption><p>Cross-study comparison of mean O<sub>3</sub>-induced FEV<sub>1</sub> decrements due to 6.6 hr of constant, S-W exposure to varied O<sub>3</sub> concentrations. All exposures were conducted in a chamber, except for a face-mask exposure to 0.04 ppm O<sub>3</sub> in the ##REF##12122573##Adams (2002)## study. All studies used a 6.6-hr exposure protocol in which volunteers alternated between 50 min of exercise (V<sub>E</sub> ≈ 20 L/min/m<sup>2</sup> BSA) and 10 min of rest with an additional 35 min of rest after the third hour. For this exposure protocol, the ##REF##17497527##McDonnell et al. (2007)## curve illustrates the predicted FEV<sub>1</sub> decrement at 6.6 hr as a function of O<sub>3</sub> concentration for a 23-year-old. Error bars (where available) are the SE of responses. The data at 0.08 and 0.12 ppm have been offset for illustrative purposes.</p></caption></fig>
<table-wrap id="t1-ehp0116-001023" position="float"><label>Table 1</label><caption><p>Percent decrement in FEV<sub>1</sub> for 6.6 hr of exposure to FA and 0.06 ppm O<sub>3</sub> for individuals in the ##REF##16393927##Adams (2006)## study.</p></caption><table frame="hsides" rules="groups"><thead><tr><th align="left" rowspan="1" colspan="1">Subject</th><th align="center" rowspan="1" colspan="1">ΔFA</th><th align="center" rowspan="1" colspan="1">ΔO<sub>3</sub></th><th align="center" rowspan="1" colspan="1">ΔO<sub>3</sub> – ΔFA</th></tr></thead><tbody><tr><td align="left" rowspan="1" colspan="1">1</td><td align="center" rowspan="1" colspan="1">−1.46</td><td align="center" rowspan="1" colspan="1">−0.87</td><td align="center" rowspan="1" colspan="1">0.59</td></tr><tr><td align="left" rowspan="1" colspan="1">2</td><td align="center" rowspan="1" colspan="1">0.20</td><td align="center" rowspan="1" colspan="1">3.01</td><td align="center" rowspan="1" colspan="1">2.81</td></tr><tr><td align="left" rowspan="1" colspan="1">3</td><td align="center" rowspan="1" colspan="1">−0.29</td><td align="center" rowspan="1" colspan="1">5.93</td><td align="center" rowspan="1" colspan="1">6.23</td></tr><tr><td align="left" rowspan="1" colspan="1">4</td><td align="center" rowspan="1" colspan="1">−5.33</td><td align="center" rowspan="1" colspan="1">−3.52</td><td align="center" rowspan="1" colspan="1">1.81</td></tr><tr><td align="left" rowspan="1" colspan="1">5</td><td align="center" rowspan="1" colspan="1">−8.62</td><td align="center" rowspan="1" colspan="1">−3.75</td><td align="center" rowspan="1" colspan="1">4.87</td></tr><tr><td align="left" rowspan="1" colspan="1">6</td><td align="center" rowspan="1" colspan="1">−2.94</td><td align="center" rowspan="1" colspan="1">−3.89</td><td align="center" rowspan="1" colspan="1">−0.95</td></tr><tr><td align="left" rowspan="1" colspan="1">7</td><td align="center" rowspan="1" colspan="1">−0.21</td><td align="center" rowspan="1" colspan="1">0.21</td><td align="center" rowspan="1" colspan="1">0.42</td></tr><tr><td align="left" rowspan="1" colspan="1">8</td><td align="center" rowspan="1" colspan="1">−0.28</td><td align="center" rowspan="1" colspan="1">3.43</td><td align="center" rowspan="1" colspan="1">3.71</td></tr><tr><td align="left" rowspan="1" colspan="1">9</td><td align="center" rowspan="1" colspan="1">−3.12</td><td align="center" rowspan="1" colspan="1">3.91</td><td align="center" rowspan="1" colspan="1">7.03</td></tr><tr><td align="left" rowspan="1" colspan="1">10</td><td align="center" rowspan="1" colspan="1">−6.32</td><td align="center" rowspan="1" colspan="1">6.43</td><td align="center" rowspan="1" colspan="1">12.76<xref ref-type="table-fn" rid="tfn2-ehp0116-001023">a</xref></td></tr><tr><td align="left" rowspan="1" colspan="1">11</td><td align="center" rowspan="1" colspan="1">−0.53</td><td align="center" rowspan="1" colspan="1">0.53</td><td align="center" rowspan="1" colspan="1">1.07</td></tr><tr><td align="left" rowspan="1" colspan="1">12</td><td align="center" rowspan="1" colspan="1">4.76</td><td align="center" rowspan="1" colspan="1">−2.66</td><td align="center" rowspan="1" colspan="1">−7.42<xref ref-type="table-fn" rid="tfn2-ehp0116-001023">a</xref></td></tr><tr><td align="left" rowspan="1" colspan="1">13</td><td align="center" rowspan="1" colspan="1">−1.71</td><td align="center" rowspan="1" colspan="1">−2.87</td><td align="center" rowspan="1" colspan="1">−1.16</td></tr><tr><td align="left" rowspan="1" colspan="1">14</td><td align="center" rowspan="1" colspan="1">−0.42</td><td align="center" rowspan="1" colspan="1">2.87</td><td align="center" rowspan="1" colspan="1">3.29</td></tr><tr><td align="left" rowspan="1" colspan="1">15</td><td align="center" rowspan="1" colspan="1">−1.16</td><td align="center" rowspan="1" colspan="1">−0.57</td><td align="center" rowspan="1" colspan="1">0.58</td></tr><tr><td align="left" rowspan="1" colspan="1">16</td><td align="center" rowspan="1" colspan="1">−5.54</td><td align="center" rowspan="1" colspan="1">−1.74</td><td align="center" rowspan="1" colspan="1">3.80</td></tr><tr><td align="left" rowspan="1" colspan="1">17</td><td align="center" rowspan="1" colspan="1">−0.62</td><td align="center" rowspan="1" colspan="1">−1.05</td><td align="center" rowspan="1" colspan="1">−0.43</td></tr><tr><td align="left" rowspan="1" colspan="1">18</td><td align="center" rowspan="1" colspan="1">−4.35</td><td align="center" rowspan="1" colspan="1">1.88</td><td align="center" rowspan="1" colspan="1">6.23</td></tr><tr><td align="left" rowspan="1" colspan="1">19</td><td align="center" rowspan="1" colspan="1">−3.17</td><td align="center" rowspan="1" colspan="1">1.98</td><td align="center" rowspan="1" colspan="1">5.15</td></tr><tr><td align="left" rowspan="1" colspan="1">20</td><td align="center" rowspan="1" colspan="1">2.02</td><td align="center" rowspan="1" colspan="1">5.03</td><td align="center" rowspan="1" colspan="1">3.00</td></tr><tr><td align="left" rowspan="1" colspan="1">21</td><td align="center" rowspan="1" colspan="1">−2.19</td><td align="center" rowspan="1" colspan="1">3.66</td><td align="center" rowspan="1" colspan="1">5.85</td></tr><tr><td align="left" rowspan="1" colspan="1">22</td><td align="center" rowspan="1" colspan="1">−2.19</td><td align="center" rowspan="1" colspan="1">−5.13</td><td align="center" rowspan="1" colspan="1">−2.93</td></tr><tr><td align="left" rowspan="1" colspan="1">23</td><td align="center" rowspan="1" colspan="1">0.21</td><td align="center" rowspan="1" colspan="1">14.73</td><td align="center" rowspan="1" colspan="1">14.52<xref ref-type="table-fn" rid="tfn2-ehp0116-001023">a</xref></td></tr><tr><td align="left" rowspan="1" colspan="1">24</td><td align="center" rowspan="1" colspan="1">−0.58</td><td align="center" rowspan="1" colspan="1">0.59</td><td align="center" rowspan="1" colspan="1">1.17</td></tr><tr><td align="left" rowspan="1" colspan="1">25</td><td align="center" rowspan="1" colspan="1">−0.27</td><td align="center" rowspan="1" colspan="1">0.54</td><td align="center" rowspan="1" colspan="1">0.81</td></tr><tr><td align="left" rowspan="1" colspan="1">26</td><td align="center" rowspan="1" colspan="1">−4.14</td><td align="center" rowspan="1" colspan="1">1.10</td><td align="center" rowspan="1" colspan="1">5.24</td></tr><tr><td align="left" rowspan="1" colspan="1">27</td><td align="center" rowspan="1" colspan="1">1.79</td><td align="center" rowspan="1" colspan="1">2.02</td><td align="center" rowspan="1" colspan="1">0.23</td></tr><tr><td align="left" rowspan="1" colspan="1">28</td><td align="center" rowspan="1" colspan="1">0.19</td><td align="center" rowspan="1" colspan="1">−0.40</td><td align="center" rowspan="1" colspan="1">−0.60</td></tr><tr><td align="left" rowspan="1" colspan="1">29</td><td align="center" rowspan="1" colspan="1">0.87</td><td align="center" rowspan="1" colspan="1">4.21</td><td align="center" rowspan="1" colspan="1">3.34</td></tr><tr><td align="left" rowspan="1" colspan="1">30</td><td align="center" rowspan="1" colspan="1">5.02</td><td align="center" rowspan="1" colspan="1">9.62</td><td align="center" rowspan="1" colspan="1">4.60</td></tr><tr><td align="left" rowspan="1" colspan="1">Mean</td><td align="center" rowspan="1" colspan="1">−1.35</td><td align="center" rowspan="1" colspan="1">1.51</td><td align="center" rowspan="1" colspan="1">2.85</td></tr><tr><td align="left" rowspan="1" colspan="1">SD</td><td align="center" rowspan="1" colspan="1">2.98</td><td align="center" rowspan="1" colspan="1">4.24</td><td align="center" rowspan="1" colspan="1">4.28</td></tr></tbody></table></table-wrap> <table-wrap id="t2-ehp0116-001023" position="float"><label>Table 2</label><caption><p>Descriptive and inferential statistics for O<sub>3</sub>-induced decrements<xref ref-type="table-fn" rid="tfn3-ehp0116-001023">a</xref> in FEV<sub>1</sub> for the full data set (<italic>n</italic> = 30) and for two data sets with potential outliers removed.</p></caption><table frame="hsides" rules="groups"><thead><tr><th align="left" rowspan="1" colspan="1"/><th colspan="3" align="center" rowspan="1">Data set
<hr/></th></tr><tr><th align="left" rowspan="1" colspan="1"/><th align="center" rowspan="1" colspan="1"><italic>n</italic> = 30</th><th align="center" rowspan="1" colspan="1"><italic>n</italic> = 29</th><th align="center" rowspan="1" colspan="1"><italic>n</italic> = 27</th></tr></thead><tbody><tr><td align="left" rowspan="1" colspan="1">Median<xref ref-type="table-fn" rid="tfn3-ehp0116-001023">a</xref></td><td align="center" rowspan="1" colspan="1">2.91%</td><td align="center" rowspan="1" colspan="1">2.81%</td><td align="center" rowspan="1" colspan="1">2.81%</td></tr><tr><td align="left" rowspan="1" colspan="1">Mean<xref ref-type="table-fn" rid="tfn3-ehp0116-001023">a</xref></td><td align="center" rowspan="1" colspan="1">2.85%</td><td align="center" rowspan="1" colspan="1">2.45%</td><td align="center" rowspan="1" colspan="1">2.44%</td></tr><tr><td align="left" rowspan="1" colspan="1">SE<xref ref-type="table-fn" rid="tfn3-ehp0116-001023">a</xref></td><td align="center" rowspan="1" colspan="1">0.78%</td><td align="center" rowspan="1" colspan="1">0.69%</td><td align="center" rowspan="1" colspan="1">0.51%</td></tr><tr><td align="left" rowspan="1" colspan="1">95% confidence interval<xref ref-type="table-fn" rid="tfn3-ehp0116-001023">a</xref></td><td align="center" rowspan="1" colspan="1">1.26–4.45%</td><td align="center" rowspan="1" colspan="1">1.03–3.87%</td><td align="center" rowspan="1" colspan="1">1.38–3.49%</td></tr><tr><td align="left" rowspan="1" colspan="1">Sign test <italic>p</italic>-value<xref ref-type="table-fn" rid="tfn4-ehp0116-001023">b</xref></td><td align="center" rowspan="1" colspan="1">0.0019</td><td align="center" rowspan="1" colspan="1">0.0030</td><td align="center" rowspan="1" colspan="1">0.0021</td></tr><tr><td align="left" rowspan="1" colspan="1">Wilcoxon <italic>p</italic>-value<xref ref-type="table-fn" rid="tfn4-ehp0116-001023">b</xref>,<xref ref-type="table-fn" rid="tfn5-ehp0116-001023">c</xref></td><td align="center" rowspan="1" colspan="1">0.0008</td><td align="center" rowspan="1" colspan="1">0.0014</td><td align="center" rowspan="1" colspan="1">0.0004</td></tr><tr><td align="left" rowspan="1" colspan="1">Paired <italic>t</italic>-test <italic>p</italic>-value<xref ref-type="table-fn" rid="tfn4-ehp0116-001023">b</xref></td><td align="center" rowspan="1" colspan="1">0.0010</td><td align="center" rowspan="1" colspan="1">0.0014</td><td align="center" rowspan="1" colspan="1">&lt;0.0001</td></tr></tbody></table></table-wrap>
<fn-group><fn><p>W.F.M. was funded by U.S. EPA contract EP07H001352.</p></fn><fn><p>Unrelated to the production of this article, W.F.M. received funding from the American Petroleum Institute to evaluate new ozone health effects data and to conduct research related to a human ozone exposure–response model. The other authors declare they have no competing financial interests.</p></fn><fn><p>This document has been reviewed in accordance with U.S. Environmental Protection Agency (EPA) policy and approved for publication. Mention of trade names or commercial products does not constitute endorsement or recommendation for use. The views expressed in this article are those of the authors and do not necessarily reflect the views or policies of the U.S. EPA.</p></fn></fn-group> <table-wrap-foot><fn id="tfn1-ehp0116-001023"><p>ΔO<sub>3</sub> – ΔFA represents the decrements due to 0.06 ppm O<sub>3</sub> corrected for any FA effects. Data are FEV<sub>1</sub> percent decrements from preexposure; a negative number indicates an increase or improvement in FEV<sub>1</sub>.</p></fn><fn id="tfn2-ehp0116-001023"><label>a</label><p>Potential outlier according to the Tukey criteria.</p></fn></table-wrap-foot> <table-wrap-foot><fn id="tfn3-ehp0116-001023"><label>a</label><p>O<sub>3</sub>-induced decrements are the difference between percent decrements in FEV<sub>1</sub> from the preexposure for the 0.06 ppm O<sub>3</sub> and FA exposures.</p></fn><fn id="tfn4-ehp0116-001023"><label>b</label><p><italic>p</italic>-Values are two sided.</p></fn><fn id="tfn5-ehp0116-001023"><label>c</label><p>Wilcoxon signed rank test.</p></fn></table-wrap-foot>
<graphic xlink:href="ehp0116-001023f1"/> <graphic xlink:href="ehp0116-001023f2"/>
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Environ Health Perspect. 2008 Aug 21; 116(8):1023-1026