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2003 National Survey on Drug Use & Health: Results |
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An important limitation of estimates of drug use prevalence from the National Survey on Drug Use and Health (NSDUH) is that they are only designed to describe the target population of the survey—the civilian, noninstitutionalized population aged 12 or older. Although this population includes almost 98 percent of the total U.S. population aged 12 or older, it excludes some important and unique subpopulations that may have very different drug use patterns. For example, the survey excludes active military personnel, who have been shown to have significantly lower rates of illicit drug use. Also, persons living in institutional group quarters, such as prisons and residential drug treatment centers, are not included in NSDUH, yet they have been shown in other surveys to have higher rates of illicit drug use. Also excluded are homeless persons not living in a shelter on the survey date; they are another population shown to have higher than average rates of illicit drug use. Appendix D describes other surveys that provide data for these populations.
The national estimates, along with the associated variance components, were computed using a multiprocedure package, SUrvey DAta ANalysis (SUDAAN) Software for Statistical Analysis of Correlated Data. SUDAAN was designed for the statistical analysis of sample survey data from stratified, multistage cluster samples (RTI, 2001). The final, nonresponse-adjusted, and poststratified analysis weights were used in SUDAAN to compute unbiased design-based drug use estimates.
The sampling error (i.e., the standard error [SE]) of an estimate is the error caused by the selection of a sample instead of conducting a census of the population. Sampling error is reduced by selecting a large sample and by using efficient sample design and estimation strategies, such as stratification, optimal allocation, and ratio estimation.
With the use of probability sampling methods in NSDUH, it is possible to develop estimates of sampling error from the survey data. These estimates have been calculated in SUDAAN for all estimates presented in this report using a Taylor series linearization approach that takes into account the effects of the complex NSDUH design features. The sampling errors are used to identify unreliable estimates and to test for the statistical significance of differences between estimates.
Estimates of means or proportions, 
, such as drug use prevalence rates, take the form of nonlinear statistics whenever the variances cannot be expressed in closed form. Variance estimation for nonlinear statistics in SUDAAN is performed using a first-order Taylor series approximation of the deviations of estimates from their expected values.
Corresponding to estimates of domain means or proportions, , the number of drug users, 
, can be estimated as
, D
where
= estimated population total for domain d, and
The SE for the total estimate is obtained by multiplying the SE of the mean or proportion by , that is,
. D
This approach is theoretically correct when the domain size estimates, , are among those forced to Census Bureau population projections through the weight calibration process (Chen et al., 2004). In these cases, is not subject to sampling error. For a more detailed explanation of the weight calibration process, see Section A.3.2 in Appendix A.
For estimated domain totals, , where is not fixed (i.e., where domain size estimates are not forced to U.S. Bureau of the Census population projections), this formulation may still provide a good approximation if it can be reasonably assumed that the sampling variation in is negligible relative to the sampling variation in . This is a reasonable assumption in most cases.
For a subset of the tables produced from the 2003 data, the above approach yielded an underestimate of the variance of a total because was subject to considerable variation. In these cases, a different method within SUDAAN was used to estimate variances. SUDAAN provides an option to directly estimate the variance of the linear statistic that estimates a population total. Using this option did not affect the SE estimates for the corresponding proportions presented in the same sets of tables.
As has been done in past NSDUH reports, direct survey estimates from the 2003 NSDUH considered to be unreliable due to unacceptably large sampling errors are not shown in this report and are noted by asterisks (*) in the tables containing such estimates. The criteria used for suppressing all direct survey estimates were based on the relative standard error (RSE) (defined as the ratio of the SE over the estimate) on nominal sample size and on effective sample size.
Proportion estimates (
) within the range [0 < < 1], rates, and corresponding estimated number of users were suppressed if
RSE[-ln()] > 0.175 when 
0.5
or
RSE[-ln(1 - )] > 0.175 when > 0.5. D
Using a first-order Taylor series approximation to estimate RSE[-ln()] and RSE[-ln(1 - )], the following was obtained and used for computational purposes:
or
The separate formulas for 0.5 and > 0.5 produce a symmetric suppression rule; that is, if is suppressed, then 1 - will be as well. This ad hoc rule requires an effective sample size in excess of 50. When 0.05 < < 0.95, the symmetric property of the rule produces a local maximum effective sample size of 68 at = 0.5. Thus, estimates with these values of along with effective sample sizes falling below 68 are suppressed. See Figure B.1 for a graphical representation of the required minimum effective sample sizes as a function of the proportion estimated.
A minimum nominal sample size suppression criterion (n = 100) that protects against unreliable estimates caused by small design effects and small nominal sample sizes was employed. Prevalence estimates also were suppressed if they were close to 0 or 100 percent (i.e., if < 0.00005 or if 
0.99995).
Estimates of other totals (e.g., number of initiates), along with means and rates that are not bounded between 0 and 1 (e.g., mean age at first use and incidence rates) were suppressed if the RSEs of the estimates were larger than 0.5. Additionally, estimates of the mean age at first use were suppressed if the sample size was smaller than 10 respondents; also, the estimated incidence rate and number of initiates were suppressed if they rounded to 0.
The suppression criteria for various NSDUH estimates are summarized in Table B.1 at the end of this appendix.
This section describes the methods used to compare prevalence estimates in this report. Customarily, the observed difference between estimates is evaluated in terms of its statistical significance. Statistical significance is based on the p value of the test statistic and refers to the probability that a difference as large as that observed would occur due to random variability in the estimates if there were no difference in the prevalence rates for the population groups being compared. The significance of observed differences in this report is generally reported at the 0.05 and 0.01 levels. When comparing prevalence estimates, the null hypothesis (no difference between prevalence rates) was tested against the alternative hypothesis (there is a difference in prevalence rates) using the standard difference in proportions test expressed as
, D
where 
= first prevalence estimate, 
= second prevalence estimate, var() = variance of first prevalence estimate, var() = variance of second prevalence estimate, and cov(, ) = covariance between and . In cases where significance tests between years were performed, the 2002 prevalence estimate becomes the first prevalence estimate and the 2003 estimate becomes the second prevalence estimate.
Under the null hypothesis, Z is asymptotically distributed as a normal random variable. Therefore, calculated values of Z can be referred to as the unit normal distribution to determine the corresponding probability level (i.e., p value). Because the covariance term is not necessarily zero, SUDAAN was used to compute estimates of Z along with the associated p values using the analysis weights and accounting for the sample design as described in Appendix A. A similar procedure and formula for Z were used for estimated totals.
When comparing population subgroups defined by three or more levels of a categorical variable, log-linear Chi-square tests of independence of the subgroup and the prevalence variables were conducted first to control the error level for multiple comparisons. If the Chi-square test indicated overall significant differences, the significance of each particular pairwise comparison of interest was tested using SUDAAN analytic procedures to properly account for the sample design. Using the published estimates and SEs to perform independent t tests for the difference of proportions will usually provide the same results as tests performed in SUDAAN. However, where the significance level is borderline, results may differ for two reasons: (1) the covariance term is included in SUDAAN tests whereas it is not included in independent t tests, and (2) the reduced number of significant digits shown in the published estimates may cause rounding errors in the independent t tests.
As part of a comparative analysis, prevalence estimates from the Monitoring the Future (MTF) study, sponsored by the National Institute on Drug Abuse (NIDA), were presented for recency measures of selected substances. The analyses focused on prevalence estimates for adults aged 19 to 28 and the average of 8th and 10th grade prevalence estimates. Published results were available from NIDA for significant differences between 2002 and 2003 prevalence estimates for adults aged 19 to 28, but not for the averaged rates for 8th and 10th graders. The difference between these averages from 2002 and 2003 was estimated and tested. The estimate of the difference of the averages can be expressed as
where 
, 
and 
are the prevalence estimates for the 8th and 10th grades, respectively, for 2002; 
is defined similarly for 2003. The variance of some prevalence estimate can be written as
where n is the sample size and D is the appropriate design effect obtained from the sampling design. In the MTF study, design effects were available for comparisons between 2002 and 2003 estimates; therefore, the variance of the difference between 2002 and 2003 estimates for a particular grade can be expressed as
where i = 1 indexes the 8th grade, i = 2 indexes the 10th grade, Di is the design effect appropriate for comparisons between 2002 and 2003 estimates, and the nji are the sample sizes corresponding to the indexed year and grade prevalence estimates. Because the 8th and 10th grade samples were independently drawn, the variance of the difference between the 8th and 10th grade averages can be expressed as
The test statistic can therefore be written as
where Z is asymptotically distributed as a standard normal random variable.
Nonsampling errors can occur from nonresponse, coding errors, computer processing errors, errors in the sampling frame, reporting errors, and other errors not due to sampling. Nonsampling errors are reduced through data editing, statistical adjustments for nonresponse, close monitoring and periodic retraining of interviewers, and improvement in various quality control procedures.
Although nonsampling errors can often be much larger than sampling errors, measurement of most nonsampling errors is difficult or impossible. However, some indication of the effects of some types of nonsampling errors can be obtained through proxy measures, such as response rates and from other research studies.
In 2003, respondents continued to receive a $30 incentive in an effort to improve response rates over years prior to 2002. Of the 143,485 eligible households sampled for the 2003 NSDUH main study, 130,605 were successfully screened for a weighted screening response rate of 90.7 percent (Table B.2). In these screened households, a total of 81,631 sample persons were selected, and completed interviews were obtained from 67,784 of these sample persons, for a weighted interview response rate of 77.4 percent (Table B.3). A total of 8,909 (14.7 percent) sample persons were classified as refusals or parental refusals, 3,051 (4.0 percent) were not available or never at home, and 1,887 (3.9 percent) did not participate for various other reasons, such as physical or mental incompetence or language barrier (see Table B.3, which also shows the distribution of the selected sample by interview code and age group). The weighted interview response rate was highest among 12 to 17 year olds (89.6 percent), females (79.0 percent), blacks and Hispanics (80.1 and 79.6 percent, respectively), in nonmetropolitan areas (79.7 percent), and among persons residing in the Midwest (78.6 percent) (Table B.4).
The overall weighted response rate, defined as the product of the weighted screening response rate and weighted interview response rate, was 70.2 percent in 2003. Nonresponse bias can be expressed as the product of the nonresponse rate (1–R) and the difference between the characteristic of interest between respondents and nonrespondents in the population (Pr - Pnr). Thus, assuming the quantity (Pr - Pnr) is fixed over time, the improvement in response rates in 2002 and 2003 over prior years will result in estimates with lower nonresponse bias.
Among survey participants, item response rates were above 99 percent for most questionnaire items. However, inconsistent responses for some items, including the drug use items, were common. Estimates of substance use from NSDUH are based on responses to multiple questions by respondents, so that the maximum amount of information is used in determining whether a respondent is classified as a drug user. Inconsistencies in responses are resolved through a logical editing process that involves some judgment on the part of survey analysts and is a potential source of nonsampling error.
NSDUH estimates are based on self-reports of drug use, and their value depends on respondents' truthfulness and memory. Although many studies have generally established the validity of self-report data and NSDUH procedures were designed to encourage honesty and recall, some degree of underreporting is assumed (Harrell, 1997; Harrison & Hughes, 1997; Rouse, Kozel, & Richards, 1985). No adjustment to NSDUH data is made to correct for this. The methodology used in NSDUH has been shown to produce more valid results than other self-report methods (e.g., by telephone) (Aquilino, 1994; Turner, Lessler, & Gfroerer, 1992). However, comparisons of NSDUH data with data from surveys conducted in classrooms suggest that underreporting of drug use by youths in their homes may be substantial (Gfroerer, 1993; Gfroerer, Wright, & Kopstein, 1997).
Several measurement issues are associated with the 2003 NSDUH that may be of interest and are discussed in this section. Specifically, these issues include the impact of questionnaire changes on trends and the methods for measuring nicotine (cigarette) dependence, substance dependence and abuse, incidence, and serious mental illness (SMI). In addition, the results of an analysis of differences in estimates for Native Hawaiians or Other Pacific Islanders in 2002 and 2003 are presented.
To maintain valid trend measurement, changes to NSDUH core questions on substance use are rarely made. However, small refinements or additions to core questions sometimes are implemented if necessary to improve the questionnaire or obtain new information, when analyses demonstrate that there will be negligible impact on the estimates for which trends are needed. In the 2003 NSDUH, two small changes within the hallucinogens module of the questionnaire were made:
With regard to the first issue, the "fill" refers to text that the computer inserts into a question based on responses to previous questions. In 2002, for respondents who reported lifetime use of LSD and a combination of "no," "don't know," or "refused" to lifetime use of all other hallucinogens, the hallucinogen name "filled" in the questions about age at first use and recency of use was "LSD." In 2003, the "fill" for these respondents was "LSD or any other hallucinogen" because of the uncertainty about their use of other hallucinogens. This same logic applied to respondents who reported use of only PCP or of only Ecstasy (MDMA) and who answered other hallucinogen questions as "don't know" or "refused." This change affected a miniscule number of respondents (three for LSD, none for PCP, and four for Ecstasy). This change was made in 2003 because respondents who did not know or refused to report whether they had ever used other hallucinogens were potentially users of these other hallucinogens. For respondents whose only use was LSD, PCP, or Ecstasy and who answered all other lifetime hallucinogen questions as "no," the respective "fills" continued to be "LSD," "PCP," or "Ecstasy."
A second small change to the questionnaire in 2003 involved the addition of follow-up questions in the hallucinogens module to capture information about the frequency of use in the past 12 months or past 30 days. If respondents reported that they last used any hallucinogen "more than 12 months ago," they were skipped out of questions related to their frequency of use in the past 12 months and past 30 days. If they then, for example, reported that they last used LSD "more than 30 days ago but within the past 12 months," that would trigger a consistency check between these two related recency questions. In 2003, if respondents revised their hallucinogen recency to indicate use more than 30 days ago but within the past 12 months, they were asked to provide the information on their frequency of use in the past 12 months. In 2002, respondents were not asked these follow-up questions in these situations. Therefore, unknown frequency of use data for these cases were replaced with statistically imputed values. In contrast, the inclusion of these follow-up questions in 2003 resulted in fewer cases having unknown frequency of use data that required imputation.
Table B.5 shows some comparisons of estimates between 2002 and 2003. Estimates were produced for 2003 with and without data from the additional follow-up questions. To produce the estimates without the additional questions, the data were reedited and reimputed without taking into account information present in these new questions.
The addition of new follow-up questions in 2003 had little effect on estimates of frequency of use in the past 12 months and past 30 days. In particular, where statistically significant differences in estimates occurred between 2002 and 2003, these differences generally were significant for both versions (with and without follow-up questions) of the 2003 estimate. There were two exceptions. The difference in the estimated of number of days (300 days or more) used hallucinogens in past year among past year users aged 18 to 25 was statistically significant between 2002 and 2003 without follow-up questions. Also, the difference in the estimate of hallucinogen use on 1 or 2 days in the past month for the population aged 12 or older was statistically significant between 2002 and 2003 without the follow-up questions. Yet these two instances do not offer enough evidence to conclude that the addition of the follow-up questions in 2003 had any effect on estimates for the 12–month or 30–day frequency of use of hallucinogens. Because there were multiple comparisons and no correction factors were used to adjust for these multiple comparisons, it is common to expect at least 5 percent of the comparisons to be statistically significant, as was seen here, even if the null hypothesis of no difference is true. Furthermore, because the data were reimputed, statistically significant differences could be attributable to differences in random variation due to imputation.1
The 2003 NSDUH computer-assisted interviewing (CAI) instrumentation included questions designed to measure nicotine dependence among current cigarette smokers. Those respondents who only smoked specialty cigarettes (bidis or cloves) in the past month were not defined as current cigarette smokers and therefore could not be defined as being nicotine dependent. Nicotine dependence is based on criteria derived from the Nicotine Dependence Syndrome Scale (NDSS) (Shiffman, Hickcox, Gnys, Paty, & Kassel, 1995; Shiffman, Waters, & Hickcox, 2004) or the Fagerstrom Test of Nicotine Dependence (FTND) (Fagerstrom, 1978; Heatherton, Kozlowski, Frecker, & Fagerstrom, 1991).
The conceptual roots of the NDSS (Edwards & Gross, 1976) are similar to those behind the American Psychiatric Association (APA) Diagnostic and Statistical Manual of Mental Disorders, 4th edition (DSM-IV), concept of dependence (APA, 1994). The 2003 NSDUH contained 19 NDSS questions that addressed five aspects of dependence:
Each of the five domains listed above can be assessed by a continuous measure, but an average score across all domains also can be obtained for overall nicotine dependence (Shiffman et al., 2004). The NDSS algorithm for calculating this average score was based on the respondent's answers to 17 of the 19 questions listed above. The two items regarding nonsmoking friends (4b and 5a) were excluded due to frequently missing data.
In order to optimize the number of respondents who could be classified for nicotine dependence, imputation was utilized for all respondents who answered all but 1 of the 17 nicotine dependence questions that were used in the NDSS algorithm. The imputation was based upon weighted least square regressions using the other 16 NDSS items as covariates in the model (Grau et al., 2003).
Responses to items 1a-c, 1e, 2a-c, 3a-c, 4a, 4c, and 5c were coded from 1 to 5 where
1 = Not at all true of me
2 = Sometimes true of me
3 = Moderately true of me
4 = Very true of me
5 = Extremely true of me
Responses to items 1d, 3d, 3e, and 5b were reverse coded from 5 to 1 where
5 = Not at all true of me
4 = Sometimes true of me
3 = Moderately true of me
2 = Very true of me
1 = Extremely true of me
The NDSS score was calculated as the sum of the responses to the previous questions divided by 17. The NDSS score was only calculated for current cigarette smokers who had complete data for all 17 questions.
A current cigarette smoker was defined as nicotine dependent if his or her NDSS score was greater than or equal to 2.75. If the NDSS score for a current cigarette smoker was less than 2.75 or the NDSS score was not defined, then the respondent was determined to be nondependent based on the NDSS. The threshold of 2.75 was derived by examining the distribution of scores in other samples of smokers administered the NDSS, including a contrast of scores obtained for nondependent smokers (chippers) versus heavy smokers (Shiffman, Paty, Kassel, Gnys, & Zettler-Segal, 1994).
The FTND is a multi-item measure of dependence, but much of its ability to discriminate dependent smokers derives from a single item that assesses how soon after waking that smokers have their first cigarette (Heatherton, Kozlowski, Frecker, Rickert, & Robinson, 1989). Because most nicotine is cleared from the bloodstream overnight, smokers typically wake in nicotine deprivation, and rapid movement to smoke is considered a sign of dependence. A current cigarette smoker was defined as nicotine dependent based on the FTND if the first cigarette smoked was within 30 minutes of waking up on the days that he or she smoked.
Using both the NDSS and the FTND measures described above, a current cigarette smoker was defined as having nicotine dependence in the past month if he or she met either the NDSS or FTND criteria for dependence.
The 2003 NSDUH CAI instrumentation included questions that were designed to measure dependence and abuse of illicit drugs and alcohol. For these substances,2 dependence and abuse questions were based on the criteria in the DSM-IV (APA, 1994).
Specifically, for marijuana, inhalants, hallucinogens, and tranquilizers, a respondent was defined as having dependence if he or she met three or more of the following six dependence criteria:
For alcohol, pain relievers, cocaine, heroin, sedatives, and stimulants, a respondent was defined as having dependence if he or she met three or more of seven dependence criteria, including the six standard criteria listed above plus a seventh withdrawal symptom criterion. The seventh withdrawal criterion is defined by a respondent reporting having experienced a certain number of withdrawal symptoms that vary by substance (e.g., having trouble sleeping, cramps, hands tremble).
For each illicit drug and alcohol, a respondent was defined as having abused that substance if he or she met one or more of the following four abuse criteria and was determined not to be dependent upon the respective substance in the past year.
Criteria used to determine whether a respondent was asked the dependence and abuse questions included responses from core substance use and frequency of substance use questions, as well as noncore substance use questions. Unknown responses in the core substance use and frequency of substance use questions were imputed. However, the imputation process did not take into account reported data in the noncore CAI modules. Responses to the dependence and abuse questions that were inconsistent with the imputed substance use or frequency of substance use could have existed. Because different criteria and different combinations of criteria were used as skip logic for each substance, different types of inconsistencies may have occurred for certain substances between responses to the dependence and abuse questions and the imputed substance use and frequency of substance use as described below.
For alcohol and marijuana, respondents were asked the dependence and abuse questions if they reported substance use in the past year but did not report their frequency of substance use in the past year. Therefore, inconsistencies could have occurred where the imputed frequency of use response indicated less frequent use than required for respondents to be asked the dependence and abuse questions originally.
For stimulants, heroin, and cocaine, respondents were asked the dependence and abuse questions if they reported past year use in a core drug module or past year use in the noncore special drugs module. Thus, inconsistencies could have occurred when the response to a core substance use indicated no use in the past year, but responses to dependence and abuse questions indicated substance dependence or abuse for the respective substance.
A respondent might have provided ambiguous information about past year use of any individual substance, in which case these respondents were not asked the dependence and abuse questions for that substance. Subsequently, these respondents could have been imputed to be past year users of the respective substance. In this situation, the dependence and abuse data were unknown; thus, these respondents were classified as not dependent on or abusing the respective substance. However, the respondent was never actually asked the dependence and abuse questions.
For diseases, the incidence rate for a population is defined as the number of new cases of the disease, N, divided by the person time, PT, of exposure or
. D
The person time of exposure can be measured for the full period of the study or for a shorter period. The person time of exposure ends at the time of diagnosis (e.g., Greenberg, Daniels, Flanders, Eley, & Boring, 1996, pp. 16–19). Similar conventions are applied for defining the incidence of first use of a substance.
Beginning in 1999, the survey questionnaire allows for collection of year and month of first use for recent initiates. Month, day, and year of birth also are obtained directly or imputed in the process. In addition, the questionnaire call record provides the date of the interview. By imputing a day of first use within the year and month of first use reported or imputed, the key respondent inputs in terms of exact dates are known. Exposure time can be determined in terms of days and converted to an annual basis. Beginning in 2003, the immigrant population was addressed in the incidence analysis. That is, immigrants who initiated drug use outside the United States were not included in this analysis. However, those immigrants who did not initiate outside the United States were included in the analysis for the time period since they entered the United States. If respondents indicated that they were not born in the United States, the survey questionnaire asked the respondent how long they had lived in the United States. Using this information, an imputation-revised entry age and date were created.
Having exact dates of birth and first use (and if the respondent is an immigrant, his or her exact date of entry) also allows the person time of exposure during the targeted period, t, to be determined. Let the target time period for measuring incidence be specified in terms of dates; for example, the period 1998 would be specified as
t = [t1,t2) = [1 Jan 1998, 1 Jan 1999), D
a period that includes 1 January 1998 and all days up to but not including 1 January 1999. The target age group also can be defined by a half-open interval as a = [a1,a2). For example, the age group 12 to 17 would be defined by a = [12,18) for persons at least age 12, but not yet age 18. If person i was in age group a and residing in the United States during period t, the time and age interval, Lt,a,i , then can be determined by the intersection:
assuming the time of birth and time of entry into the United States can be written in terms of day (DOBi and DOEi), month (MOBi and MOEi), and year (YOBi and YOEi). Either this intersection will be empty (Lt,a,i = 
), or it will be designated by the half-open interval, Lt,a,i = [M1,i,M2,i), where
m1,i = Max{t1,(DOBiMOBiYOBi + a1), DOEiMOEiYOEi} D
and
m2,i = Min{t2,(DOBiMOBiYOBi + a2)}. D
The date of first use, tfu,d,i, also is expressed as an exact date. An incident of first drug d use by person i in age group a occurs in time tfu,d,i 
[m1,i,m2,i). The indicator function Ii(d,a,t) used to count incidents of first use is set to 1 when tfu,d,i [m1,i,m2,i) and to 0 otherwise. The person-time exposure measured in years and denoted by ei(d,a,t) for a person i of age group a depends on the date of first use. If the date of first use precedes the target period (tfu,d,i < m1,i), then ei (d,a,t) = 0. If the date of first use occurs after the target period or if person i has never used drug d, then
. D
If the date for first use occurs during the target period Lt,a,i, then
, D
Note that both Ii(d,a,t) and ei(d,a,t) are set to 0 if the target period Lt,a,i is empty (i.e., person i is not in age group a during any part of time t). The incidence rate then is estimated as a weighted ratio estimate:
, D
where the wi are the analytic weights. Starting in 2002, estimates were reported separately for males and females, as well as overall. For a more detailed explanation of the incidence methodology, see Packer, Odom, Chromy, Davis, and Gfroerer (2002).
The estimates of incidence in this report are based on retrospective reports of age at first drug use by survey respondents interviewed during 2002 and 2003. Because they are based on retrospective reports, they may be subject to different types of biases. Bias due to differential mortality occurs because some persons who were alive and exposed to the risk of first drug use in the historical periods shown in the tables died before the 2002 and 2003 NSDUHs were conducted. This bias is probably very small for estimates shown in this report. Incidence estimates also are affected by memory errors, including recall decay (tendency to forget events occurring long ago) and forward telescoping (tendency to report that an event occurred more recently than it actually did). Recall decay would tend to result in a downward bias in estimates for earlier years (e.g., 1960s and 1970s), and telescoping would tend to result in an upward bias for estimates for more recent years. There also is likely to be some underreporting bias due to social acceptability of drug use behaviors and respondents' fear of disclosure. This is likely to have the greatest impact on recent estimates, which reflect more recent use and reporting by younger respondents. Finally, for drug use that is frequently initiated at age 10 or younger, estimates based on retrospective reports 1 year later underestimate total incidence because 11–year–old (and younger) children are not sampled by NSDUH. Prior analyses showed that alcohol and cigarette (any use) incidence estimates could be significantly affected by this. Therefore, for these drugs, only 2002 age-specific rates and the number of initiates aged 18 or older (or 21 or older for applicable tables) were reported. Likewise, for these drugs, 2001 and 2002 estimates were made using 2003 NSDUH data only.
A recent evaluation of NSDUH retrospective estimates of incidence suggests that these types of bias are significant and differ by substance and length of recall (Gfroerer, Hughes, Chromy, Heller, & Packer, 2004). For very recent time periods, bias in estimates of marijuana, cocaine, alcohol, and cigarettes appears to be small, but for all other substances there is significant downward bias. Bias for all substances increases the further back in time the estimates are made, suggesting a relationship with the length of recall. Due to the potential reporting biases described above, comparisons between years, particularly between recent estimates and those 10 or more years prior, should be made with caution.
For the 2003 NSDUH, mental health among adults was measured using a scale to ascertain serious mental illness (SMI). This scale consisted of six questions that asked respondents how frequently they experienced symptoms of psychological distress during the 1 month in the past year when they were at their worst emotionally. The use of this scale is based on a methodological study designed to evaluate several screening scales for measuring SMI in NSDUH. These scales consisted of a truncated version of the World Health Organization (WHO) Composite International Diagnostic Interview Short Form (CIDI-SF) scale (Kessler, Andrews, Mroczek, Üstün, & Wittchen, 1998), the K10/K6 scale of nonspecific psychological distress (Furukawa, Kessler, Slade, & Andrews, 2003), and the WHO Disability Assessment Schedule (WHO-DAS) (Rehm et al., 1999).
The methodological study to evaluate the scales consisted of 155 respondents selected from a first-stage sample of 1,000 adults aged 18 or older. First-stage respondents were selected from the Boston metropolitan area and screened on the telephone to determine whether they had any emotional problems. Respondents reporting emotional problems at the first stage were oversampled when selecting the 155 respondents at the second stage. The selected respondents were interviewed by trained clinicians in respondents' homes using both the NSDUH methodology and a structured clinical interview. The first interview included the three scales described above using audio computer-assisted self-interviewing (ACASI). Respondents completed the ACASI portion of the interview without discussing their answers with the clinician. After completing the ACASI interview, respondents then were interviewed using the 12–month nonpatient version of the Structured Clinical Interview for DSM-IV (SCID) (First Spitzer, Gibbon, & Williams, 1997) and the Global Assessment of Functioning (GAF) (Endicott, Spitzer, Fleiss, & Cohen, 1976) to classify respondents as either having or not having SMI.
The data from the 155 respondents were analyzed using logistic regression analysis to predict SMI from the scores on the screening questions. Analysis of the model fit indicated that each of the scales alone and in combination were significant predictors of SMI and the best fitting models contained either the CIDI-SF or the K10/K6 alone. Receiver operating characteristic (ROC) curve analysis was used to evaluate the precision of the scales to discriminate between respondents with and without SMI. This analysis indicated that the K6 was the best predictor. The results of the methodological study and the K10/K6 scale of nonspecific psychological distress are described in more detail in Kessler et al. (2003).
To score the six items on the K6 scales, they were first coded from 0 to 4 and summed to yield a number between 0 and 24. This involved transforming response categories for the six questions (DSNERV1, DSHOPE, DSFIDG, DSNOCHR, DSEFFORT, and DSDOWN) given below so that "all of the time" was coded 4, "most of the time" was coded 3, "some of the time" 2, "a little of the time" 1, and "none of the time" 0, with "don't know" and "refuse" also coded 0. Summing across the transformed responses resulted in a score with a range from 0 to 24. Respondents with a total score of 13 or greater were classified as having a past year SMI. This cutpoint was chosen to equalize false positives and false negatives.
The questions comprising the K6 scale are given as follows:
During that month, how often did you feel nervous?
Response categories are the same for the following questions:
Large differences in the estimated rate of SMI for the non-Hispanic Native Hawaiian or Other Pacific Islander (NH/OPI) group were observed between the 2002 and 2003 NSDUHs. Although not statistically significant, the estimated rate of SMI increased from 5.4 to 12.4 percent for this group between the 2 years. There also was a large decrease between 2002 and 2003 in the estimated number of people in the NH/OPI category, from 813,000 in 2002 to 490,000 in 2003.
The reasons for these differences were investigated, first by verifying the weighting and estimation procedures that had been used and then by examining the distributions of weights and weight components. It appears that the differences between years are due to a lack of stability in the estimates of the number of people in the NH/OPI group. The U.S. Bureau of the Census estimate of the number of people in the NH/OPI group was about 311,000 in 2000, a very small proportion of the U.S. population. In general, for small population groups, there can be large variability from year to year in the number of persons who are randomly selected for NSDUH and in estimates of substance use and mental health. Poststratification can be used to control the year-to-year variability in the estimated number of people in a particular group. This is done by adjusting the sum of the weights for particular groups to an independent census estimate of the number in that group for the time period in question. However, NSDUH does not currently poststratify to independent estimates of NH/OPI.
More specifically, the differences between 2002 and 2003 arose because relative to 2002, fewer people in 2003 in the older age groups identified themselves as Other Pacific Islanders. Breaking the NH/OPI sample down into NH and OPI shows that the larger weighted count of NH/OPI in 2002 compared with 2003 was due to a larger OPI count for that year. Table B.6 presents the unweighted and weighted counts and percentage distributions by age group for the NH and OPI groups aged 18 or older by year. The weighted number of NH respondents remained fairly consistent between the 2 years, but the number of OPI respondents decreased from 587,033 in 2002 to 274,735 in 2003. This was due to the relatively greater share of older OPI respondents in 2002. In 2002, there were 31 OPI respondents aged 35 or older representing a weighted total of 372,297 persons, but in 2003, there were only 11 OPI respondents aged 35 or older representing a weighted total of 83,399 persons.
In addition, analyses were conducted to examine whether there was a shift in the number of persons reporting more than one race between 2002 and 2003. Persons claiming two or more races in 2002 and 2003 were examined by Hispanicity and by whether they claimed NH/OPI as one of their races. Although more respondents claimed two or more races in 2003 than in 2002, there was not a large shift in the number who included NH/OPI as one of their races.
Given the instability in the estimated number of people selecting the NH/OPI category, the impact on additional estimates from the survey was examined for 2002 and 2003. Lifetime, past year, and past month any illicit drug use, marijuana use, cocaine use, and any hallucinogen use were examined. An additional item, driving while under the influence of any illicit drugs in the past year, was examined because it was the only variable in the detailed NSDUH tables for which there were significant differences for the NH/OPI racial group between the 2 years and that included all age groups. (Comparisons for other variables also were significant, but those variables were collected only for 12 to 17 year olds.)
Table B.7 presents the results of these comparisons. The only significant differences between the 2 years were found in the weighted estimates of driving under the influence of drugs for all NH/OPI respondents aged 18 or older (3.1 percent in 2002 and 9.7 percent in 2003) and for the 18 to 25 age group (6.4 percent in 2002 and 21.4 percent in 2003).
| Estimate | Suppress if: |
|---|---|
| Prevalence rate, , with nominal sample size, n, and design effect, deff |
(1) The estimated prevalence rate, , is < 0.00005 or 0.99995, or
(2) (3) Effective n < 100, where Effective N = (4) n < 100. Note: The rounding portion of this suppression rule for prevalence rates will produce some estimates that round at one decimal place to 0.0 or 100.0 percent but are not suppressed from the tables. |
| Estimated number (numerator of ) |
The estimated prevalence rate, , is suppressed.
Note: In some instances when |
Mean age at first use,  , with nominal sample size, n |
(1) RSE() > 0.5, or
(2) n < 10. |
Incidence rate,  |
(1) The incidence rate, , rounds to < 0.1 per 1,000 person-years of exposure, or
(2) RSE( |
Number of initiates,  |
(1) The number of initiates , rounds to < 1,000 initiates, or
(2) RSE( |
| Source: SAMHSA, Office of Applied Studies, National Survey on Drug Use and Health, 2003. | |
| Sample Size | Weighted Percentage | |||
|---|---|---|---|---|
| 2002 | 2003 | 2002 | 2003 | |
| Total Sample | 178,013 | 170,762 | 100.00 | 100.00 |
| Ineligible cases | 27,851 | 27,277 | 15.27 | 15.84 |
| Eligible cases | 150,162 | 143,485 | 84.73 | 84.16 |
| Ineligibles | 27,851 | 27,277 | 15.27 | 15.84 |
| Vacant | 14,417 | 14,588 | 51.55 | 52.56 |
| Not a primary residence | 4,580 | 4,377 | 17.36 | 17.07 |
| Not a dwelling unit | 2,403 | 2,349 | 8.16 | 8.08 |
| All military personnel | 289 | 356 | 1.08 | 1.39 |
| Other, ineligible | 6,162 | 5,607 | 21.86 | 20.90 |
| Eligible Cases | 150,162 | 143,485 | 84.73 | 84.16 |
| Screening complete | 136,349 | 130,605 | 90.72 | 90.72 |
| No one selected | 80,557 | 74,310 | 53.14 | 51.04 |
| One selected | 30,738 | 30,702 | 20.58 | 21.46 |
| Two selected | 25,054 | 25,593 | 17.00 | 18.22 |
| Screening not complete | 13,813 | 12,880 | 9.28 | 9.28 |
| No one home | 3,031 | 2,446 | 2.02 | 1.68 |
| Respondent unavailable | 411 | 280 | 0.26 | 0.18 |
| Physically or mentally incompetent | 307 | 290 | 0.20 | 0.18 |
| Language barrier—Hispanic | 66 | 42 | 0.05 | 0.03 |
| Language barrier—Other | 461 | 450 | 0.35 | 0.39 |
| Refusal | 8,556 | 8,414 | 5.86 | 5.98 |
| Other, access denied | 471 | 923 | 0.30 | 0.81 |
| Other, eligible | 12 | 12 | 0.01 | 0.01 |
| Resident < 1/2 of quarter | 0 | 0 | 0.00 | 0.00 |
| Segment not accessible | 0 | 0 | 0.00 | 0.00 |
| Screener not returned | 15 | 16 | 0.01 | 0.01 |
| Fraudulent case | 479 | 6 | 0.21 | 0.00 |
| Electronic screening problem | 4 | 1 | 0.00 | 0.00 |
| Source: SAMHSA, Office of Applied Studies, National Survey on Drug Use and Health, 2002 and 2003. | ||||
| Final Interview Code | Persons Aged 12 or Older | Persons Aged 12 to 17 | Persons Aged 18 or Older | |||||||||
|---|---|---|---|---|---|---|---|---|---|---|---|---|
| Sample Size | Weighted Percentage | Sample Size | Weighted Percentage | Sample Size | Weighted Percentage | |||||||
| 2002 | 2003 | 2002 | 2003 | 2002 | 2003 | 2002 | 2003 | 2002 | 2003 | 2002 | 2003 | |
| Total | 80,581 | 81,631 | 100.00 | 100.00 | 26,230 | 25,387 | 100.00 | 100.00 | 54,351 | 56,244 | 100.00 | 100.00 |
| Interview Complete | 68,126 | 67,784 | 78.56 | 77.39 | 23,659 | 22,696 | 89.99 | 89.57 | 44,467 | 45,088 | 77.20 | 75.96 |
| No One at Dwelling Unit | 1,359 | 1,242 | 1.81 | 1.60 | 182 | 158 | 0.70 | 0.62 | 1,177 | 1,084 | 1.94 | 1.71 |
| Respondent Unavailable | 1,893 | 1,809 | 2.71 | 2.44 | 329 | 310 | 1.20 | 1.25 | 1,564 | 1,499 | 2.89 | 2.58 |
| Break-Off | 48 | 33 | 0.10 | 0.09 | 9 | 2 | 0.04 | 0.01 | 39 | 31 | 0.11 | 0.10 |
| Physically/Mentally Incompetent | 692 | 755 | 1.75 | 1.82 | 161 | 150 | 0.57 | 0.60 | 531 | 605 | 1.89 | 1.96 |
| Language Barrier - Hispanic | 138 | 177 | 0.19 | 0.21 | 9 | 6 | 0.04 | 0.02 | 129 | 171 | 0.21 | 0.23 |
| Language Barrier - Other | 327 | 364 | 1.09 | 1.13 | 24 | 11 | 0.13 | 0.07 | 303 | 353 | 1.21 | 1.25 |
| Refusal | 6,276 | 7,433 | 12.73 | 14.10 | 464 | 486 | 1.81 | 1.74 | 5,812 | 6,947 | 14.03 | 15.56 |
| Parental Refusal | 1,307 | 1,476 | 0.55 | 0.61 | 1,307 | 1,476 | 5.15 | 5.81 | 0 | 0 | 0.00 | 0.00 |
| Other | 415 | 558 | 0.52 | 0.62 | 86 | 92 | 0.38 | 0.31 | 329 | 466 | 0.53 | 0.65 |
| Source: SAMHSA, Office of Applied Studies, National Survey on Drug Use and Health, 2002 and 2003. | ||||||||||||
| Selected Persons | Completed Interviews | Weighted Response Rate | ||||
|---|---|---|---|---|---|---|
| 2002 | 2003 | 2002 | 2003 | 2002 | 2003 | |
| Total | 80,581 | 81,631 | 68,126 | 67,784 | 78.56% | 77.39% |
| Age in Years | ||||||
| 12–17 | 26,230 | 25,387 | 23,659 | 22,696 | 89.99% | 89.57% |
| 18–25 | 27,216 | 27,259 | 23,271 | 22,941 | 85.16% | 83.47% |
| 26 or older | 27,135 | 28,985 | 21,196 | 22,147 | 75.81% | 74.63% |
| Gender | ||||||
| Male | 39,453 | 40,008 | 32,766 | 32,627 | 77.06% | 75.72% |
| Female | 41,128 | 41,623 | 35,360 | 35,157 | 79.99% | 78.96% |
| Race/Ethnicity | ||||||
| Hispanic | 10,250 | 10,753 | 8,692 | 8,985 | 80.93% | 79.55% |
| White | 55,594 | 55,958 | 46,834 | 46,294 | 78.23% | 77.21% |
| Black | 9,385 | 9,466 | 8,143 | 8,099 | 82.24% | 80.12% |
| All other races | 5,352 | 5,454 | 4,457 | 4,406 | 70.50% | 69.88% |
| Region | ||||||
| Northeast | 16,490 | 16,736 | 13,706 | 13,655 | 75.57% | 75.20% |
| Midwest | 22,588 | 22,665 | 19,180 | 18,993 | 80.01% | 78.56% |
| South | 24,530 | 24,725 | 20,900 | 20,612 | 79.99% | 78.38% |
| West | 16,973 | 17,505 | 14,340 | 14,524 | 77.33% | 76.51% |
| County Type | ||||||
| Large metropolitan | 32,294 | 36,610 | 26,792 | 29,759 | 76.85% | 75.49% |
| Small metropolitan | 28,121 | 27,661 | 23,944 | 23,349 | 79.50% | 79.51% |
| Nonmetropolitan | 20,166 | 17,360 | 17,390 | 14,676 | 81.38% | 79.72% |
| Source: SAMHSA, Office of Applied Studies, National Survey on Drug Use and Health, 2002 and 2003. | ||||||
| Frequency of Use | Total | AGE GROUP (Years) | ||||||||||
|---|---|---|---|---|---|---|---|---|---|---|---|---|
| 12–17 | 18–25 | 26 or Older | ||||||||||
| 2002 | 2003 with Follow-Up Questions |
2003 without Follow-Up Questions |
2002 | 2003 with Follow-Up Questions |
2003 without Follow-Up Questions |
2002 | 2003 with Follow-Up Questions |
2003 without Follow-Up Questions |
2002 | 2003 with Follow-Up Questions |
2003 without Follow-Up Questions |
|
| Number of Days Used in Past Year among Past Year Users | ||||||||||||
| 1–11 | 72.4 | 73.3 | 73.7 | 63.5 | 67.2 | 65.2 | 74.2 | 74.8 | 74.9 | 75.5 | 74.9 | 77.6 |
| 12–49 | 18.4 | 17.0 | 16.0 | 22.0 | 19.4 | 20.6 | 17.7 | 16.4 | 16.2 | 17.1 | 16.4 | 12.1 |
| 50–99 | 6.1 | 5.8 | 6.5 | 8.3 | 7.5 | 8.1 | 4.8 | 5.9 | 6.4 | 7.0 | 4.3 | 5.3 |
| 100–299 | 3.1 | 3.4 | 3.4 | 6.0 | 5.1 | 5.3 | 3.2 | 2.5 | 2.0 | 0.4 | * | * |
| 300 or More | 0.1 | 0.5a | 0.5a | 0.2 | 0.7 | 0.7 | 0.1 | 0.5 | 0.6a | * | 0.3 | 0.3 |
| Number of Days Used in Past Month among Past Month Users | ||||||||||||
| 1–2 | 81.1 | 75.0 | 74.0a | 63.6 | 74.6a | 75.1a | 77.8 | 76.8 | 76.3 | * | * | * |
| 3–5 | 13.3 | 14.6 | 15.2 | 21.9 | 9.8b | 9.9b | 17.4 | 15.3 | 15.9 | * | * | * |
| 6–19 | 3.9 | 8.9a | 9.2a | 11.5 | 13.4 | 12.8 | 2.8 | 6.2a | 6.0a | * | * | * |
| 20 or More | 1.7 | 1.5 | 1.5 | 2.9 | 2.3 | 2.2 | 2.1 | 1.7 | 1.8 | * | * | * |
| *Low precision; no estimate reported. a Difference between estimate and 2002 estimate is statistically significant at the 0.05 level. b Difference between estimate and 2002 estimate is statistically significant at the 0.01 level. Source: SAMHSA, Office of Applied Studies, National Survey on Drug Use and Health, 2002 and 2003. |
||||||||||||
| Age | 2002 | 2003 | ||||||
|---|---|---|---|---|---|---|---|---|
| Unweighted | Weighted | Unweighted | Weighted | |||||
| n | % | n | % | n | % | n | % | |
| NH | ||||||||
| 18+ | 61 | 144,415 | 67 | 140,171 | ||||
| 18–25 | 25 | 40.98% | 18,296 | 12.67% | 31 | 46.27% | 19,229 | 13.72% |
| 26–34 | 15 | 24.59% | 44,960 | 31.13% | 11 | 16.42% | 36,362 | 25.94% |
| 35–49 | 13 | 21.31% | 53,081 | 36.76% | 20 | 29.85% | 48,640 | 34.70% |
| 50+ | 8 | 13.11% | 28,079 | 19.44% | 5 | 7.46% | 35,940 | 25.64% |
| OPI | ||||||||
| 18+ | 129 | 587,033 | 101 | 274,735 | ||||
| 18–25 | 83 | 64.34% | 151,238 | 25.76% | 77 | 76.24% | 139,834 | 50.90% |
| 26–34 | 15 | 11.63% | 63,498 | 10.82% | 13 | 12.87% | 51,502 | 18.75% |
| 35–49 | 21 | 16.28% | 128,071 | 21.82% | 8 | 7.92% | 29,056 | 10.58% |
| 50+ | 10 | 7.75% | 244,226 | 41.60% | 3 | 2.97% | 54,343 | 19.78% |
| Source: SAMHSA, Office of Applied Studies, National Survey on Drug Use and Health, 2002 and 2003. | ||||||||
| Measure | Age Group | 2002 | 2003 | 2002 Versus 2003 (Based on ANALWT) | ||||||
|---|---|---|---|---|---|---|---|---|---|---|
| n | Un-weighted | Weighted | n | Un-weighted | Weighted | Difference of Mean | SE (Difference) | P value | ||
| Serious Mental Illness | ||||||||||
| Past Year | 18+ | 190 | 11.58% | 5.44% | 168 | 11.90% | 12.42% | -6.99% | 4.01% | 0.11 |
| (18–25) | 108 | 14.81% | 14.27% | 108 | 12.04% | 17.58% | -3.31% | 7.11% | 0.65 | |
| (26–34) | 30 | 6.67% | 4.31% | 24 | 8.33% | 12.25% | -7.95% | 10.38% | 0.46 | |
| (35+) | 52 | 7.69% | 2.40% | 36 | 13.89% | 7.62% | -5.22% | 4.15% | 0.23 | |
| Any Illicit Drug | ||||||||||
| Lifetime | Overall | 273 | 54.21% | 44.21% | 252 | 53.17% | 51.01% | -6.81% | 8.37% | 0.4318 |
| (12–17) | 83 | 38.55% | 36.10% | 84 | 35.71% | 35.85% | 0.24% | 10.94% | 0.9825 | |
| (18–25) | 108 | 66.67% | 65.12% | 108 | 58.33% | 51.72% | 13.41% | 8.42% | 0.1373 | |
| (26–34) | 30 | 60.00% | 72.96% | 24 | 70.83% | 72.30% | 0.65% | 15.26% | 0.9666 | |
| (35+) | 52 | 50.00% | 30.98% | 36 | 66.67% | 46.01% | -15.03% | 14.67% | 0.3258 | |
| Past Year | Overall | 273 | 27.11% | 17.02% | 252 | 25.40% | 18.53% | -1.51% | 5.28% | 0.7805 |
| (12–17) | 83 | 26.51% | 19.02% | 84 | 25.00% | 22.53% | -3.51% | 8.28% | 0.6788 | |
| (18–25) | 108 | 36.11% | 35.08% | 108 | 32.41% | 31.40% | 3.68% | 8.84% | 0.6847 | |
| (26–34) | 30 | 20.00% | 18.02% | 24 | 12.50% | 15.02% | 2.99% | 13.87% | 0.8327 | |
| (35+) | 52 | 13.46% | 9.67% | 36 | 13.89% | 6.37% | 3.30% | 6.19% | 0.6038 | |
| Past Month | Overall | 273 | 12.45% | 7.89% | 252 | 15.08% | 11.10% | -3.21% | 3.63% | 0.3938 |
| (12–17) | 83 | 14.46% | 11.02% | 84 | 16.67% | 14.63% | -3.61% | 6.79% | 0.6040 | |
| (18–25) | 108 | 12.04% | 9.55% | 108 | 18.52% | 16.93% | -7.38% | 6.17% | 0.2552 | |
| (26–34) | 30 | 13.33% | 14.94% | 24 | 4.17% | 11.14% | 3.80% | 13.81% | 0.7877 | |
| (35+) | 52 | 9.62% | 5.01% | 36 | 8.33% | 3.97% | 1.04% | 3.98% | 0.7977 | |
| Marijuana | ||||||||||
| Lifetime | Overall | 273 | 45.05% | 35.88% | 252 | 46.83% | 47.54% | -11.66% | 8.18% | 0.1797 |
| (12–17) | 83 | 24.10% | 17.63% | 84 | 19.05% | 17.22% | 0.41% | 7.77% | 0.9590 | |
| (18–25) | 108 | 61.11% | 62.68% | 108 | 57.41% | 50.55% | 12.13% | 8.42% | 0.1754 | |
| (26–34) | 30 | 56.67% | 71.97% | 24 | 66.67% | 70.97% | 1.00% | 15.34% | 0.9493 | |
| (35+) | 52 | 38.46% | 20.52% | 36 | 66.67% | 46.01% | -25.49% | 13.94% | 0.0925 | |
| Past Year | Overall | 273 | 17.58% | 9.36% | 252 | 19.05% | 12.95% | -3.59% | 3.54% | 0.3298 |
| (12–17) | 83 | 15.66% | 7.41% | 84 | 14.29% | 13.11% | -5.71% | 6.73% | 0.4132 | |
| (18–25) | 108 | 26.85% | 28.40% | 108 | 27.78% | 26.07% | 2.32% | 8.65% | 0.7930 | |
| (26–34) | 30 | 16.67% | 17.03% | 24 | 8.33% | 3.89% | 13.15% | 9.37% | 0.1859 | |
| (35+) | 52 | 1.92% | 0.76% | 36 | 11.11% | 5.20% | -4.44% | 3.16% | 0.1856 | |
| Past Month | Overall | 273 | 8.79% | 4.42% | 252 | 10.71% | 7.28% | -2.87% | 2.52% | 0.2765 |
| (12–17) | 83 | 9.64% | 5.87% | 84 | 9.52% | 10.62% | -4.74% | 6.39% | 0.4725 | |
| (18–25) | 108 | 11.11% | 8.79% | 108 | 14.81% | 13.23% | -4.44% | 5.62% | 0.4441 | |
| (26–34) | 30 | 13.33% | 14.94% | 24 | 0.00% | 0.00% | 14.94% | 9.05% | 0.1249 | |
| (35+) | 52 | 0.00% | 0.00% | 36 | 8.33% | 3.97% | -3.97% | 2.74% | 0.1738 | |
| Cocaine | ||||||||||
| Lifetime | Overall | 273 | 12.45% | 12.61% | 252 | 12.70% | 18.57% | -5.96% | 5.83% | 0.3266 |
| (12–17) | 83 | 4.82% | 1.80% | 84 | 3.57% | 10.18% | -8.38% | 6.20% | 0.2016 | |
| (18–25) | 108 | 11.11% | 9.77% | 108 | 11.11% | 12.99% | -3.22% | 5.59% | 0.5758 | |
| (26–34) | 30 | 30.00% | 35.25% | 24 | 12.50% | 17.75% | 17.50% | 16.65% | 0.3139 | |
| (35+) | 52 | 17.31% | 10.21% | 36 | 38.89% | 28.05% | -17.84% | 11.39% | 0.1431 | |
| Past Year | Overall | 273 | 2.93% | 2.39% | 252 | 2.78% | 4.25% | -1.86% | 2.66% | 0.4965 |
| (12–17) | 83 | 3.61% | 1.19% | 84 | 2.38% | 4.92% | -3.73% | 4.52% | 0.4252 | |
| (18–25) | 108 | 2.78% | 3.48% | 108 | 3.70% | 4.63% | -1.15% | 3.43% | 0.7434 | |
| (26–34) | 30 | 6.67% | 11.60% | 24 | 4.17% | 11.14% | 0.46% | 13.66% | 0.9737 | |
| (35+) | 52 | 0.00% | 0.00% | 36 | 0.00% | 0.00% | 0.00% | 0.00% | . | |
| Past Month | Overall | 273 | 1.10% | 0.61% | 252 | 1.19% | 3.50% | -2.89% | 2.26% | 0.2250 |
| (12–17) | 83 | 1.20% | 0.21% | 84 | 1.19% | 4.55% | -4.34% | 4.44% | 0.3469 | |
| (18–25) | 108 | 0.93% | 1.50% | 108 | 0.93% | 2.49% | -0.99% | 2.86% | 0.7349 | |
| (26–34) | 30 | 3.33% | 2.10% | 24 | 4.17% | 11.14% | -9.04% | 10.59% | 0.4100 | |
| (35+) | 52 | 0.00% | 0.00% | 36 | 0.00% | 0.00% | 0.00% | 0.00% | . | |
| Any Hallucinogen | ||||||||||
| Lifetime | Overall | 273 | 13.19% | 11.86% | 252 | 14.29% | 11.56% | 0.30% | 4.40% | 0.9467 |
| (12–17) | 83 | 8.43% | 3.81% | 84 | 4.76% | 5.22% | -1.41% | 4.88% | 0.7777 | |
| (18–25) | 108 | 15.74% | 15.86% | 108 | 21.30% | 23.55% | -7.68% | 7.44% | 0.3220 | |
| (26–34) | 30 | 16.67% | 21.77% | 24 | 12.50% | 4.51% | 17.26% | 10.68% | 0.1320 | |
| (35+) | 52 | 13.46% | 9.45% | 36 | 16.67% | 6.75% | 2.71% | 6.40% | 0.6800 | |
| Past Year | Overall | 273 | 3.30% | 1.12% | 252 | 3.57% | 3.18% | -2.06% | 1.51% | 0.1982 |
| (12–17) | 83 | 4.82% | 2.87% | 84 | 3.57% | 5.19% | -2.33% | 4.82% | 0.6375 | |
| (18–25) | 108 | 3.70% | 2.66% | 108 | 5.56% | 7.36% | -4.70% | 4.06% | 0.2699 | |
| (26–34) | 30 | 3.33% | 2.10% | 24 | 0.00% | 0.00% | 2.10% | 2.06% | 0.3285 | |
| (35+) | 52 | 0.00% | 0.00% | 36 | 0.00% | 0.00% | 0.00% | 0.00% | . | |
| Past Month | Overall | 273 | 0.00% | 0.00% | 252 | 0.79% | 0.76% | -0.76% | 0.70% | 0.3025 |
| (12–17) | 83 | 0.00% | 0.00% | 84 | 2.38% | 4.92% | -4.92% | 4.44% | 0.2898 | |
| (18–25) | 108 | 0.00% | 0.00% | 108 | 0.00% | 0.00% | 0.00% | 0.00% | . | |
| (26–34) | 30 | 0.00% | 0.00% | 24 | 0.00% | 0.00% | 0.00% | 0.00% | . | |
| (35+) | 52 | 0.00% | 0.00% | 36 | 0.00% | 0.00% | 0.00% | 0.00% | . | |
| Driving Under Influence of Any Illicit Drugs | ||||||||||
| Past Year | Overall | 273 | 5.49% | 3.10% | 252 | 11.51% | 9.67% | -6.57% | 2.69% | 0.0307* |
| (12–17) | 83 | 3.61% | 1.46% | 84 | 7.14% | 7.62% | -6.16% | 4.83% | 0.2262 | |
| (18–25) | 108 | 7.41% | 6.35% | 108 | 18.52% | 21.39% | -15.04% | 6.43% | 0.0375* | |
| (26–34) | 30 | 10.00% | 5.44% | 24 | 4.17% | 2.44% | 3.00% | 2.82% | 0.3077 | |
| (35+) | 52 | 1.92% | 1.61% | 36 | 5.56% | 3.28% | -1.67% | 2.90% | 0.5774 | |
| * Difference significant at the p < 0.05 level. Source: SAMHSA, Office of Applied Studies, National Survey on Drug Use and Health, 2002 and 2003. |
||||||||||
1 More details concerning random imputation can be found in Grau et al. (2003).
2 Substances include alcohol, cocaine, heroin, pain relievers, sedatives, marijuana, tranquilizers, stimulants, hallucinogens, and inhalants.
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