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J Acquir Immune Defic Syndr. Author manuscript; available in PMC 2013 December 1.

Published in final edited form as:

PMCID: PMC3705732

NIHMSID: NIHMS411246

Xiaojie Huang,^{a,}^{*} Hui Chen,^{b,}^{*} Wei Li,^{a} Haiying Li,^{a} Xia Jin,^{c,}^{¶} Alan S. Perelson,^{d} Zoe Fox,^{e} Tong Zhang,^{a} Xiaoning Xu,^{a} and Hao Wu^{a,}^{¥}

The publisher's final edited version of this article is available at J Acquir Immune Defic Syndr

See other articles in PMC that cite the published article.

HIV viral load set point has long been used as a prognostic marker of disease progression and more recently as an end-point parameter in HIV vaccine clinical trials. The definition of set point, however, is variable. Moreover, the earliest time at which the set point is reached after the onset of infection has never been clearly defined.

In this study, we obtained sequential plasma viral load data from 60 acutely HIV-infected Chinese patients among a cohort of men who have sex with men (MSM), mathematically determined viral load set point levels, and estimated time to attain set point after infection. We also compared the results derived from our models and that obtained from an empirical method.

With novel uncomplicated mathematic model, we discovered that setpoint may vary from 21 to 119 days dependent on the patients' initial viral load trajectory. The viral load set points were 4.28 ± 0.86 and 4.25 ± 0.87 log10 copies/ml (*P* = 0.08), respectively, as determined by our model and an empirical method, suggesting an excellent agreement between the old and new methods.

We provide a novel method to estimate viral load set point at the very early stage of HIV infection. Application of this model can accuratly and reliably determine set point, thus providing a new tool for physicians to better monitor early intervention strategies in acutely infected patients, and scientists to rationally design preventative vaccine studies.

HIV viral load set point has long been used as a predictor of disease progression ^{[1-4]}, and more recently as a parameter of HIV vaccine efficacy ^{[5]}. The definition of viral load set point, however, is more variable. During the early phase of primary HIV-1 infection, plasma viral load increases sharply by several orders of magnitude to a peak in the first few weeks post-infection, then drops rapidly within months to a relatively stable level, which has been called the viral load set point ^{[3]}. HIV-infected individuals who have a higher viral load set point have a faster progression to AIDS and death ^{[3, 6-8]}. However, most data on the timing and clinical relevance of HIV-1 viral load set points have come from studies in North America, Europe and Africa^{[9-15]}. To date, no longitudinal studies have been performed to examine the viral load set point in acute HIV-1 infected Chinese, who have a different genetic background from those of other races. In addition, there is no consensus on the time at which set point is reached due to modest numbers of subjects with well-defined dates of acquisition of infection or seroconversion, limited frequency of sampling in most acute infection cohorts, and more recently the use of early ART following infection acquisition which precludes determination of the natural evolution to set-point. In one study, plasma viral load set point was loosely defined as the viral load measured between 4–24 months after HIV-1 infection ^{[1, 3, 16]}. Alternatively, it was estimated using a method that calculates the average of all measurements taken after 4 months since the onset of infection, and with the assumption that all these observations were in the steady state ^{[3, 17]}. However, neither of the two methods can estimate the exact time at which viral load set point is attained.

In this study, we collected longitudinal clinical and laboratory data from patients with acute HIV-1 infection, and then used regression models to estimate the viral load set point values, and the exact time at which set point was attained. Our data showed that time to viral load set point after onset of infection was variable, but earlier than reported in other studies. This study also provides unique information for therapeutic and vaccine clinical trials to be conducted in Chinese patients.

This study used subjects from an ongoing prospective clinical cohort study of primary HIV-1-infected individuals in Beijing (Wu et al, unpublished data). Starting in October 2006, men who have sex with men (MSM) were enrolled into a longitudinal prospective cohort study if they were at least 18 years old and HIV-negative at baseline. After enrollment, these HIV-negative men were monitored every 2 months for plasma HIV antibodies, HIV RNA levels, and clinical signs of acute infection. The subjects for whom the HIV antibody status was negative or indeterminate but positive by nucleic acid amplification testing were defined as having acute HIV-1 infection^{[12]}. Whole blood specimens were collected at week 1, 2, 4, 8 and 12, and then every three months thereafter from detection of seroconversion, and used to separate plasma, serum and peripheral blood mononuclear cells (PBMCs). None of the subjects were treated by ART during acute HIV infection. The study was approved by the Beijing YouAn Hospital Research Ethics Committee, and written informed consent was obtained from each subject.

Subjects with <4 available samples within the first 4 months after estimated date of HIV-1 infection were excluded. No HIV-1 RNA viral load determination after the initiation of therapy was included in the analysis. Overall, 87 individuals were diagnosed with Primary HIV Infection (PHI) who were estimated to have been infected in the mid-point between the last seronegative and the first seropositive. According to the estimated date of acquisition of HIV infection, they were divided into three groups: (A) 17 with an ELISA negative while HIV RNA positive, who were estimated that HIV-1 infection occurred 17 days before the first sample was found to be positive for HIV RNA in these patients based on a published algorithm[9]; (B) 25 with an indeterminate western blot who were estimated to have been infected 30 days prior to the index or enrollment specimen; and (C) 45 with a negative for HIV-1 antibody and also negative for HIV-1 RNA followed by a seropositive and RNA positive with a time between tests < 2 months. The study population had an average age of 33.2 (SD: 9.5) years at enrollment, a median of 7 (range, 4–14) sequential viral load measurements, and a median follow-up length of 283 days (range, 80–698 days).

Standard HIV type 1 (HIV-1) ELISA (Abbott recombinant HIV-1/2 3rd generation, Vironostika HIV Uni-Form II plus O) and western blot analysis (Genelabs, HIV Blot2.2, AE2029) kits were used for antibody tests. Plasma HIV-1 RNA copies were measured by a quantitative RT-PCR HIV-1 RNA test (Roche Cobas Amplicor HIV-1 Monitor Test). Samples that tested RNA positive with HIV-1 copy numbers below the limit of quantitation (400 copies/ml) were assigned a value of 200 copies/ml for statistical purposes.

Suppose there are *m* untreated HIV-infected patients, each with *n _{i}* viral load measurements with

Let *T _{S}^{i}* and

A linear segmented regression of viral load from the time since infection was fitted for each individual, to obtain estimates of the parameters (*T _{S}^{i}*,

We modeled the dynamic changes of viral load using a mathematical equation that has as many as four terms. The first term describes a linear increase to the viral load peak. The second term describes a linear decline of viral load from the peak to a nadir concentration. The third term describes a subsequent slight linear increase of viral load to the set-point. The last term corresponds to the steady phase of the change of viral load, during which the viral load approaches a stable value. For this last term, a constant viral load was used. In clinical practice, however, one or more parts of this idealized viral load pattern may not be observed in some patients. Thus, we eliminated terms corresponding to missing parts of the pattern. All the possible viral load kinetic patterns in our observations are illustrated in Fig. 1.

Using the above terms, assumptions and notations, we obtained the following six equations:

$${Y}_{\mathit{\text{ij}}}={\mathit{\text{V}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}}+{\beta}_{0}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{P}}}^{\mathit{\text{i}}},0)+{\beta}_{1}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{N}}}^{\mathit{\text{i}}},0)+{\beta}_{2}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)+{\beta}_{3}\mathit{\text{max}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)$$

(1)

$${Y}_{\mathit{\text{ij}}}={\mathit{\text{V}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}}+{\beta}_{0}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{P}}}^{\mathit{\text{i}}},0)+{\beta}_{1}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)+{\beta}_{3}\mathit{\text{max}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)$$

(2)

$${Y}_{\mathit{\text{ij}}}={\mathit{\text{V}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}}+{\beta}_{1}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{N}}}^{\mathit{\text{i}}},0)+{\beta}_{2}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)+{\beta}_{3}\mathit{\text{max}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)$$

(3)

$${Y}_{\mathit{\text{ij}}}={\mathit{\text{V}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}}+{\beta}_{1}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)+{\beta}_{3}\mathit{\text{max}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)$$

(4)

$${Y}_{\mathit{\text{ij}}}={\mathit{\text{V}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}}+{\beta}_{2}\mathit{\text{min}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)+{\beta}_{3}\mathit{\text{max}}({t}_{\mathit{\text{ij}}}-{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)$$

(5)

$${Y}_{\mathit{\text{ij}}}={\mathit{\text{V}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}}+{\beta}_{3}\mathit{\text{max}}({t}_{\mathit{\text{ij}}}\text{\u2212}{\mathit{\text{T}}}_{\mathit{\text{S}}}^{\mathit{\text{i}}},0)$$

(6)

where *β*_{1} < 0 and *β*_{2} and *β*_{0} > 0 in these models were the rates of the decline and the increment of viral load, respectively. *β*_{3} was the change in rate of viral load in the steady period. In general, individuals with viral load decline or increment of <0.5 log_{10} copies/ml in 6 months were defined as having achieved steady state. Thus, if the absolute value of *β*_{3} was <0.0027 log_{10} copies/ml/day (i.e. 1 log_{10} copies/ml/year), the viral loads were defined as achieving the steady state and the viral set point could then be obtained. Otherwise, the individual was defined as having experienced failure to reach a steady state, and no viral set point could be estimated.

Models (1)– (6) represent the kinetic patterns 1–6 shown in Fig 1a–f, respectively. After we obtained estimates of all the parameters that appeared in one of the six models by fitting the model to data for the *i*th patient using least squares regression, estimates of the viral load peak *V _{P}^{i}* and nadir

Another goal of this study was to compare mathematical regression models with the empirical method to measure the value of the viral load set point. We also calculated the set point as the average of all measurements taken at 4 months after infection according to the empirical model ^{[4]}.

All values were given as mean ± SD in log10 units. Paired samples *t* test was used to test for difference in viral set points estimated by the two methods. *P*<0.05 (two-sided) was considered statistically significant.

To examine the absolute agreement between the viral set points estimated by using the proposed viral load kinetic models and those estimated by the empirical method, the Lin's concordance correlation coefficient (CCC) ^{[18]} was calculated as well as the location shift and scale shift of the CCC. Visual assessment of agreement was obtained by the use of Bland–Altman plots ^{[19,20]}.

Statistical analyses were done with SPSS for Windows version 15.0 (SPSS, Chicago, IL, USA) and GraphPad Prism version 5.01 for Windows (GraphPad Software, San Diego, CA, USA). The fitness of the viral load kinetic models and the estimation of parameters were done with MATLAB version 7.6 (MathWorks, Natick, MA, USA).

One of the six models discussed in the Materials and Methods section was used to estimate viral loads in all 87 enrolled patients (Fig. 1). Eighteen patients had either an increase or a decrease in viral load for more than 0.0027 log10 copies/ml/day, meaning that their viral load failed to reach a steady state. Another example of failure to reach a steady state was that viral load fluctuated beyond ±0.5 log10 copies/ml around the estimated levels of the steady state of viral loads for at least three times in a period of at least 3 months. Nine patients experienced this type of fluctuation and their viral load set points were not estimated. All these 27 patients failed to reach the steady state, resulting in being unable to estimate their viral load set points (two representative longitudinal viral load measurements in patients who failed to reach the steady state are shown in Fig. 2).

Among the 60 remaining patients, 22 patients, grouped into Group I, had already reached the steady state at the first measurement post-infection (as shown in Fig.1f). Therefore, the time to steady state could not be estimated due to a lack of significant changes of all the observed viral loads for these patients. Then the rest 38 patients whose viral load set point could be estimated were grouped into Group II.

The results on the three kinds of outcome, i.e. being able to estimate both the viral load setpoint and the time to reach the setpoint, being able to estimate only the viral load setpoint, and failing to reach the steady state, are listed in Table 2.

For the 60 patients who had achieved steady state, viral load set points were estimated as 4.28 ± 0.86 log10 copies/ml (range, 2.16–5.72 log10 copies/ml) by using our kinetic models. Viral load set points were estimated at the range of 2.73–5.55 log10 copies/ml (mean ± SD: 4.42 ± 0.80 log10 copies/ml) and 2.16–5.72 log10 copies/ml (mean ± SD: 4.19 ± 0.89 log10 copies/ml) for patients in Group I (*n* = 22) and Group II (*n* = 38), respectively. Sixty individuals were divided into three classes with differential progression by using our kinetic models. They are 18(30%), 29(48%) and 13(22%) that have viral load set point of <10,000, 10,000~100,000 and >100,000copies/ml, respectively. Times to achieve the viral load set point for Group I patients were not calculated because their viral load had already reached the steady state at the first measurement post-infection. Times to viral load set point after infection for the 38 patients in Group II were estimated at the range of 21–119 days (mean ± SD: 63.8 ± 27.1 days) (Fig. 3). For the 38 patients in Group II whose time to viral load set point could be estimated, 7.9% (3/38, 95% CI: 2.7–20.8%), 50.0% (19/38, 95% CI: 34.9–65.1%), 18.4% (7/38, 95% CI: 9.2–33.4%) and 23.7% (9/38, 95% CI: 13.0–39.2%) of them have reached viral load steady state within 30 days, 31–60 days, 61–90 days and after 90 days, respectively. In other words, a patient had a 50% probability of reaching viral load set point between 31 and 60 days, and had a 76.3% probability of reaching viral load set point within 90 days.

To validate our new method, we compared its estimates with those of a published method ^{[4]}. For the 60 patients who had achieved the steady state, their viral load set points were estimated as 4.28 ± 0.86 log10 copies/ml (range, 2.16–5.72 log10 copies/ml) by using our kinetic models, compared to 4.25 ± 0.87 log10 copies/ml (range, 2.16–5.82 log10 copies/ml) by the empirical method published by others ^{[4]}.Table 1 presents the absolute agreement assessment between our new model and the empirical method by addressing means as well as scale and location components of the CCC for each group. The bias correction factors for Group I and Group II and total were all very close to 1, meaning that the best-fit lines deviated very little from the perfect fit 45° line (measurement of accuracy) (Fig. 4a).

The Bland–Altman plots that assess agreement between our new model and the empirical method are shown in Fig. 4b. About 90.9% (20/22), 92.1% (35/38) and 93.3% (56/60) of the differences between each pair of estimated viral load set points, lay within the 95% limits of agreement for Group I, Group II and total, respectively. No significant systematic bias was observed, i.e. the average differences between paired viral load set points were all close to zero.

Our study described a novel model to estimate viral load set point in patients with acute HIV infection. It is general acknowledged that viral load set point is one of the key predictors for disease progression and prognosis of HIV-1 infection^{[12,21-23]}. The concept has more recently be applied to gauge the efficacy of preventative HIV vaccine by comparing early post infection set points in cases of breakthrough infections in vaccines with set points in infected persons in the control arm of the studies ^{[24]}. Therefore, precise determination of the set point is important for the field. The current approach for estimating the viral load set point is to measure a series of viral loads at 4 month and later after the initial detection of infection, and then calculate their average level which is defined as the set point. This is acceptable since frequently the set point is reached after 4 months of HIV infection ^{[3,5,17,25]}. However, this method can only be used to obtain viral load set point level after the acute phase of HIV infection, which is an important window for viral reservoir formation and rapidity of HIV transmission. To date, there is no model available to estimate time to development of set points or predict distributions of VLs within the acute phase of HIV infection.

In this study, we presented a novel set of mathematical models to predict viral load set point early during the acute phase of HIV infection. There are a number of strengths of our data and models. First, to generate this model, we used a large series of viral load measurements that were collected as early as week 1 after acute infection when patients were still HIV antibody negative, but RNA positive. For each subject, all the viral load measurements were put into one or more mathematic models to estimate the viral load set point and the time to reach that set point. Second, for subjects who were already in the steady state at the time of the first test, the average of all the viral load measurements was considered as the set point, but the time to set point could not be estimated due to the lack of significant change of all the observed viral loads. Third, for those who had not reached the steady state at the first measurement but finally reached that state, viral load kinetics was used to estimate the set point and the time to reach it, as well as the peak and nadir of the viral load if present. Another advantage of our method is that the set point was estimated based on all observed viral loads. Thus, our approach is more systematic than the current used empirical method which only uses the viral loads at 4 month and later after the onset of infection to estimate the viral load set point ^{[3, 5, 17]}.

To evaluate the validity of our new method, we compared results derived from our models and those that were obtained using the empirical method in our patient cohort. By using our method and that of Fellay et al ^{[4]}, viral load set points were calculated to be 4.28 ± 0.86 and 4.25 ± 0.87 log10 copies/ml (*P* = 0.08), respectively. Consistency between the two methods was further tested by CCC measurement, which showed >95% in agreement. Additional tests with CCC on means, scales and location components of each group showed a bias correction factor very close to 1, which also indicates excellent agreement between the two methods. Moreover, we used Bland–Altman plots to compare these two set of viral load set points further, and again the results showed no significant systematic bias. Finally, viral load set points were estimated to be at 4.42 ± 0.80 and 4.19 ± 0.89 log10 copies/ml for subjects who were already in a steady state in the first test (Group I), and who had not reached a steady state during the first test (Group II), respectively. Both numbers are comparable to the results by using different methods reported in previous studies ^{[19, 22, 26]}. These results demonstrate that our novel method is as accurate and reliable as the existing methods.

Our new method has an additional advantage of being able to estimate the time to reach viral load set point after infection in each individual, whereas empirical methods ^{[3, 5, 17]} can only analyze a group of individuals. Furthermore, our method eliminates the influence of patient's failure to adhere to the scheduled follow-up visits during which critical viral load measurements are obtained to estimate the viral load set point. Lastly, the time to reach viral load set point was estimated to be between 21–119 days (63.8 ± 27.1 days) in the present study, which was earlier than the commonly accepted 120 days in primarily Caucasian patient cohort ^{[6][27-29]}. However, whether these results are attributable to different modeling methods or a reflection of different patient populations remains to be studied.

There are limitations to this study. The results were obtained from a relatively limited number of cases. Therefore, our models could benefit from additional verification in a larger prospective study of acute HIV-1 infection. Despite a lack of perfection, it would be interesting to apply our newly developed models to HIV vaccine study or therapeutic clinical trials.

In summary, we have demonstrated a novel approach to estimate viral load set point at the very early stage of HIV infection. Application of this method may help physicians to gain insight into early intervention strategies that prevent viral reservoir formation and viral transmission in acutely HIV-infected patients. Its application may also help scientists to more rationally design end-point measures for HIV vaccine trials.

This study was supported in part by Major Project of Beijing Municipal Science and Technology Committee (D09050703590901), the National 12th Five-Year Major Projects of China (2012ZX10001-003, 2012ZX10001-006), and Beijing Key Laboratory (BZ0089). Portions of this work were done under the auspices of the U.S. Department of Energy under contract DE-AC52-06NA25396 and supported by NIH grants AI028433, and RR006555 (ASP).

Work attributed to Beijing PRIMO Cohort Study Group

Study conception and design (Hao Wu and Xiaoning Xu). PRIMO Cohort follow-up and data collection (Xiaojie Huang). Screening test for HIV infection (Zhiying Liu, Feili Wei and Yunxia Ji). Data collection for HIV-1 negative MSM individuals (Tong Zhang, Haiying Li, Yan Fu and Wei Xia). Sample collection and storage (Huiping Yan, Xin Zhang and Weihua Li). Pooling HIV-1RNA test results (Yan Jiang, Hong Shang and PinLiang Pan). Establishing and validating mathematic models (Hui Chen and Xiaojie Huang). Drafting the manuscript (Hui Chen, Wei Li, Xia Jin and Alan Perelson).

All authors contributed to manuscript revisions and provided advice on data analysis and interpretation.

Conflicts of interest: None

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