|Home | About | Journals | Submit | Contact Us | Français|
Objective To examine the relation between plasma HIV-1 RNA concentrations in the community and HIV incidence among injecting drug users.
Design Prospective cohort study.
Setting Inner city community in Vancouver, Canada.
Participants Injecting drug users, with and without HIV, followed up every six months between 1 May 1996 and 30 June 2007.
Main outcome measures Estimated community plasma HIV-1 RNA in the six months before each HIV negative participant’s follow-up visit. Associated HIV incidence.
Results Among 622 injecting drug users with HIV, 12435 measurements of plasma HIV-1 RNA were obtained. Among 1429 injecting drug users without HIV, there were 155 HIV seroconversions, resulting in an incidence density of 2.49 (95% confidence interval 2.09 to 2.88) per 100 person years. In a Cox model that adjusted for unsafe sexual behaviours and sharing used syringes, the estimated community plasma HIV-1 RNA concentration remained independently associated with the time to HIV seroconversion (hazard ratio 3.32 (1.82 to 6.08, P<0.001), per log10 increase). When the follow-up period was limited to observations after 1 January 1988 (when the median plasma HIV RNA concentration was <20000 copies/ml), the median viral load was no longer statistically associated with HIV incidence (1.70 (0.79 to 3.67, P=0.175), per log10 increase).
Conclusions A longitudinal measure of community plasma HIV-1 RNA concentration was correlated with the community HIV incidence rate and predicted HIV incidence independent of unsafe sexual behaviours and sharing used syringes. If these findings are confirmed, they could help to inform both HIV prevention and treatment interventions.
Since the mid-1990s, there have been major advances in the medical management of HIV infection. In particular, highly active antiretroviral therapy (HAART) has led to substantial reductions in HIV related morbidity and mortality.1 As HAART is known to effectively reduce a patient’s plasma HIV RNA concentration,2 it has been debated whether or not antiretroviral therapy can reduce HIV transmission.3 4 5 6 While several mathematical models have suggested this might be the case, researchers have suggested that the increasing use of HAART might lead to increased HIV risk behaviour, which could overwhelm the possible protective effect of HAART.3 4 5 6 Empirical data are urgently needed to inform this controversy, particularly given the recent negative results of clinical trials involving leading candidates in the microbicide and vaccine specialties.7 8 The topic has been a focus of recent academic meetings of HIV experts,9 and the World Health Organization recently released a consensus statement in which using HAART for HIV prevention was identified as a top policy-relevant research question.10
To date, no study has described the real world relation between community plasma HIV RNA concentrations and HIV incidence. This is an important gap in knowledge because the potential of HAART to reduce HIV incidence has attracted growing international interest,5 6 11 and the ongoing debates over the possible impact of increasing access to HAART might be hindering global efforts to increase its use.6 12 We therefore tested the hypothesis that a longitudinal estimate of community plasma HIV-1 RNA concentration would be associated with an estimate of community HIV incidence independent of HIV risk behaviours, such as sharing used syringes and engaging in unsafe sexual practices.
Between 1 May 1996 and 30 June 2007, injecting drug users with and without HIV were recruited into a prospective cohort study from the Downtown Eastside neighbourhood of Vancouver, Canada. Individuals were recruited regardless of HIV status and followed up every six months. Two virtual cohorts were created at the database level to independently assess incidence of HIV and plasma viral load. Those without HIV at baseline made up the Vancouver Injection Drug Users Study (VIDUS), an open prospective cohort of injecting drug users described in detail previously.13 14 Those with HIV-1 made up another cohort known as the Barriers to Accessing Antiretroviral Therapy (BART).15 16 Briefly, at baseline participants gave blood samples for HIV serology and completed a questionnaire administered by an interviewer and then returned every six months for follow-up evaluation. Extensive outreach methods with snowball sampling techniques17 18 were used to derive a representative sample. Individuals who agreed to participate were offered $C20 at each study visit. Because of the extent of poverty in the neighbourhood, as well as the nursing and support services offered through the study, the estimated refusal rate for participation in the study was under 10%.19
We estimated community plasma HIV-1 RNA concentrations every six months using data from BART cohort participants recruited from 1 May 1996 to 30 June 2007. Plasma HIV-1 RNA concentration was measured with the Roche Amplicor Monitor assay (Roche Molecular Systems, Mississauga, Canada). All plasma HIV-1 RNA samples collected from BART participants at follow-up were used to derive a longitudinal estimate of the plasma HIV-1 RNA concentration in the community over time. As previously described,15 16 the local setting is quite unusual in that there is a centralised antiretroviral dispensation programme and HIV/AIDS laboratory, allowing for a complete prospective profile of plasma HIV-1 RNA levels and use of antiretroviral therapy among cohort participants.
In addition, to determine explanations for changing concentrations of community plasma HIV-1 RNA during follow-up, we assessed use of antiretrovirals among BART participants during each year of the study and analysed changes during the study period using the Mantel test for trend.
We used similar standardised follow-up methods every six months (that is, twice a year) to estimate the annual HIV incidence among participants recruited into the VIDUS cohort. As previously described,14 HIV infection was assessed at each follow-up visit, and the date of HIV seroconversion was estimated with the midpoint between the last negative and the first positive antibody test result. We considered all participants with at least one follow-up visit to determine HIV incidence, and participants who remained persistently HIV seronegative were censored at the time of their most recent HIV antibody test result before 30 June 2007. HIV tests reactive on enzyme linked immunosorbent assay at St Paul’s Hospital were confirmed by western blotting at the British Columbia Centre for Disease Control.
To assess for a possible crude correlation between the twice a year estimates of community plasma HIV-1 RNA and the twice a year estimates of community HIV incidence, we first divided the study period into six month intervals and used the Spearman rank order correlation coefficient to assess for statistical correlation. In addition, to present the data visually, we also plotted the median plasma HIV RNA concentrations and the incidence density every six months for each year of the study and presented the uncertainty around these estimates by calculating 95% confidence intervals.20 For the estimates of HIV incidence, we calculated 95% confidence intervals using the Poisson distribution. For the estimates of median plasma HIV-RNA concentration, we calculated non-parametric two sided 95% confidence intervals by non-parametric methods based on the ordered plasma HIV-1 RNA concentrations.
We also used Cox proportional hazards regression to assess factors associated with the time to HIV infection and examined whether the estimated community plasma HIV-1 RNA concentration in the six months before each participant’s follow-up visit was associated with HIV-1 incidence, while adjusting for HIV risk behaviour. Specifically, to assess for potential confounding, we calculated unadjusted and adjusted hazard ratios of HIV infection per log10 increase in the estimated community plasma HIV-1 RNA concentration. The multivariate model was fitted with an a priori defined modelling approach whereby we examined the hazard ratio for HIV-1 RNA after adjustment for HIV risk behaviours and previously identified potential confounders. Specifically, we adjusted for sharing used syringes (yes versus no), unsafe sex (insertive or receptive anal or vaginal intercourse without a condom versus no unsafe sex), ethnicity (white versus other), cocaine use (≥ daily versus < daily), heroin use (≥ daily versus < daily), and unstable housing (living in a single room occupancy hotel, shelter, recovery or transition house, jail, on the street, or having no fixed address versus having stable housing). As with the estimated community plasma HIV-1 RNA concentration, all behavioural variables were time updated based on the data of the twice a year questionnaire and refer to the six months before the interview. All behavioural variable definitions were identical to previous reports.13 14 To assess for explanations for changes in plasma HIV RNA concentrations over time, we linked participants to the local province-wide antiretroviral dispensation programme to examine patterns of antiretroviral use during the study period. Analyses were conducted with SAS 9.1 (Cary, NC) and the threshold for significance was set at P<0.05. All P values were two sided.
Table 1 shows the baseline characteristics of the cohorts of participants with and without HIVHIV.. The baseline age was similar between the two cohorts (36.6 v 36.1 years), whereas those with HIV were more likely to be female (250 (40.2%) v 464 (32.5%)) and of non-white ethnicity (270 (43.4%) v 530 (37.1%)).
During the study period, 622 BART participants underwent plasma HIV-1 RNA assessments, among whom 250 (40.2%) were women and the median age was 37 (interquartile range 30-43). Among the 622 participants, there were 12435 plasma HIV-1 RNA assessments, with a median of 17 (8-31) measurements per person. The figure shows the estimated median plasma HIV-1 RNA concentrations every six months for 1996-20071996-2007.
During the study period, 1796 individuals who were HIV negative at baseline were enrolled into the VIDUS cohort. Of these, 367 (20.4%) were lost to follow-up before re-assessment of HIV infection and were therefore excluded from further analysis. Those lost to follow-up were more likely to be white (P=0.012), but there were no age or sex differences (both P>0.05). Among the 1429 individuals included in the HIV incidence analyses, 464 (32.5%) were women, the median age was 36.1 (27.2-42.4), and the median number of follow-up visits was 8 (3-16). During the study period, there were 155 HIV seroconversions, resulting in an overall incidence density of 2.49 (95% confidence interval 2.09 to 2.88) per 100 person years. The figure shows the incidence density for every six months for 1996-2007.1996-2007.
As implied by the patterns in the figure, when we divided the 11 year study period into 22 six month intervals, the median plasma HIV-1 RNA concentration and the HIV-1 incidence were correlated (Spearman correlation coefficient 0.48; P=0.024).
In unadjusted Cox regression analyses, we found that the median estimated community plasma HIV-1 RNA concentration during the six months before each HIV negative participant’s follow-up visit was associated with HIV seroconversion (hazard ratio 3.57 (2.03 to 6.27), P<0.001, per log10 increase). As shown in table 2, in a multivariate model that adjusted for sharing used syringes, unsafe sex, ethnicity, daily cocaine use, daily heroin use, and unstable housing, the median plasma HIV-1 RNA concentration during the six months before each HIV negative participant’s follow-up visit remained independently associated with the time to HIV seroconversion (hazard ratio 3.32 (1.82 to 6.08), P<0.001, per log10 increase).increase). In a post-hoc analysis, which limited follow-up to the period after 1 January 1988 (when the median plasma HIV RNA concentration was <20000 copies/ml), we found that the median viral load was no longer significantly associated with HIV incidence (1.70 (0.79 to 3.67), P=0.175, per log10 increase).
When we assessed for explanations for the observed longitudinal pattern of estimated community plasma HIV-1 RNA (figure), we found that the number of individuals who had started antiretroviral therapy increased during the study period from 42.5% in 1996 to 69.6% in 2007 (Mantel test for trend across all 11 years P<0.001). Among those receiving antiretroviral drugs, we found that the number using at least three antiretroviral drugs (versus fewer than three drugs) in their antiretroviral regimen increased during the study period from 8.4% in 1996 to 98.8% in 2007 (Mantel test for trend across all 11 years P<0.001).
In a small urban neighbourhood with high rates of injecting drug use, we found that estimated community plasma HIV-1 RNA concentration predicted estimated community HIV incidence, and that this association was independent of HIV risk behaviours and other potential confounders. Previous studies have suggested that injecting drug users might be less likely to access antiretroviral therapy because of physicians’ concerns related to lifestyle issues and reduced antiretroviral adherence.21 If our findings are confirmed, outreach strategies could be used to improve access to HAART among this population in an effort to reduce the HIV incidence. Any benefit of earlier use of HAART, however, must be balanced with antiretroviral toxicities and potential for increased antiretroviral resistance.22
Our study was observational, and the observed declines in HIV incidence in the community might not be causally related to the observed decline in the estimated community plasma viral load. It is nonetheless compelling that the effect of plasma HIV-1 RNA on HIV incidence was independent of time updated measurements of HIV risk behaviours, drug use patterns, and other possible confounders. Several lines of evidence support the hypothesis that community plasma HIV-1 RNA concentrations might be among the factors that determine community HIV incidence. Most importantly, HAART has been shown to reduce HIV-1 RNA concentrations in blood,23 the female genital tract,24 the rectum,25 and semen,26 which might make those with HIV less likely to transmit the virus.5 An ecological study from Taiwan showed that the expanded use of HAART was associated with a greater than 50% reduction in new HIV cases.27 Similarly, a study from Uganda, which examined couples serodiscordant for HIV, found no cases of HIV transmission where the index case had an HIV-1 RNA concentration below 1500 copies/ml.28 Interestingly, we found that the association between plasma viral load and HIV incidence was no longer significant in subanalyses restricted to the period when the median viral load reached <20000 copies/ml. This finding introduces some uncertainty into our overall finding as it suggests that our results are largely driven by the early years, during which the plasma viral load was high. The relation between viral load and HIV incidence might be less strong when viral load is below a certain threshold. Alternatively, as this is an observational study, an unmeasured confounding variable might explain the association, and the results in this subanalysis might not have been consistent because this confounding variable did not have a consistent effect throughout the follow-up period.
Our analyses were also limited by the fact that there is a known delay between HIV exposure and seroconversions, and, consistent with most studies on HIV incidence, we had to estimate an individual’s date of HIV seroconversion as the midpoint between the last negative HIV test and the first positive test.14 As a result, HIV seroconversions might have happened slightly earlier than the year to which they were assigned in our study. Regarding this limitation, it is interesting that the highest rate of HIV seroconversion was observed in the year after the highest community plasma HIV-1 RNA concentration. Antiretroviral resistance is unlikely to explain our findings as increased resistance is associated with use of less potent antiretrovirals and increasing viral load,29 30 whereas during the study period we observed the use of more potent antiretroviral therapy and decreased plasma HIV RNA concentrations. Finally, although we used extensive outreach methods and snowball sampling techniques in an effort to derive a representative sample,17 18 injecting drug users are a highly marginalised and hidden population, and we do not know with certainty that our cohort is representative of injecting drug users in the community. Previous studies have suggested the demographics of our cohort are consistent with other samples of the city’s injecting drug users,31 and it is noteworthy that our study encompasses about 30% of the estimated 4700 injecting drug users living in the neighbourhood (unpublished report, Health Canada, 1998). Although the question of the impact of a community’s plasma HIV-1 RNA concentration on HIV incidence might be better answered by a study design that randomised communities to differing levels of HAART use, such an approach might present ethical challenges because of HAART’s known effects on reducing mortality, and these data are not presently available.
We have shown that a longitudinal measure of community plasma HIV-1 RNA concentration correlates with the community HIV incidence rate and can predict HIV incidence independent of unsafe sexual behaviours and sharing syringes. These data should prompt a re-examination of arguments that dichotomise HIV prevention and HIV treatment, as they might not be independent strategies to reduce the rate of new HIV infections.6 12 These data should also help to inform the debates regarding global increase in use of antiretrovirals and possible unintended negative impacts of expanded HAART use on HIV risk behaviour and new HIV infections, as expanded HAART use in the community was associated with both reduced community plasma HIV RNA concentrations and subsequent HIV incidence.3 4 5 6
We thank the VIDUS and BART participants, and Deborah Graham, Tricia Collingham, and Kelly Hsu for their research and administrative assistance.
Contributors: EW designed the study, wrote the initial draft of the manuscript, and is guarantor. RZ and KL conducted the statistical analyses. All authors contributed to the design of the study and the drafting of the manuscript.
Funding: The VIDUS and BART studies are supported by US National Institutes of Health grants R01DA011591 and R01DA021525 and by Canadian Institutes of Health Research grant MOP-79297. TK is supported by a Canadian Institutes of Health Research (CIHR) new investigator award and a Michael Smith Foundation for Health Research (MSFHR) scholar award. BDLM is supported by a doctoral research award from CIHR and a MSFHR senior trainee award. JSGM has received an Avant-Garde award (DP1 DA026182) from the National Institute of Drug Abuse, National Institutes of Health. The authors affirm the independence of the researchers from the funders.
Competing interests: RSH has received funding for research and continuing medical education programmes from pharmaceutical companies, including Abbott, Boehringer Ingelheim, and GlaxoSmithKline. JSGM has received educational grants from, served as an ad hoc adviser to, or spoken at various events sponsored by Abbott Laboratories, Agouron Pharmaceuticals, Boehringer Ingelheim Pharmaceuticals, Borean Pharma AS, Bristol-Myers Squibb, DuPont Pharma, Gilead Sciences, GlaxoSmithKline, Hoffmann-La Roche, Immune Response Corporation, Incyte, Janssen-Ortho, Kucera Pharmaceutical Company, Merck Frosst Laboratories, Pfizer Canada, Sanofi Pasteur, Shire Biochem, Tibotec Pharmaceuticals, and Trimeris.
Ethical approval: The research was approved by the University of British Columbia’s research ethics board at St Paul’s Hospital.
Cite this as: BMJ 2009;338:b1649