Pediatric Infectious Disease Journal:
Comparing Haemophilus influenzae Type b Conjugate Vaccine Schedules: A Systematic Review and Meta-analysis of Vaccine Trials
Low, Nicola MD*; Redmond, Shelagh M. PhD*; Rutjes, Anne W. S. PhD*†; Martínez-González, Nahara A. MSc*‡; Egger, Matthias MD*; di Nisio, Marcello PhD§¶; Scott, Pippa PhD*
From the *Institute of Social and Preventive Medicine, University of Bern, Bern, Switzerland; †Center for Aging Sciences (Ce.S.I.), G. d’Annunzio University, Chieti, Italy; ‡Institute of General Practice and Health Services Research, University of Zürich, Zürich, Switzerland; §Department of Medical, Oral and Biotechnological Sciences, G. d'Annunzio University Foundation, Chieti, Italy; and ¶Department of Vascular Medicine, Academic Medical Center, Amsterdam, the Netherlands.
Accepted for publication May 28, 2013
N.L. and S.M.R. contributed equally.
The authors alone are responsible for the views expressed in this publication, and they do not necessarily represent the decisions, policy or views of the World Health Organization.
Address for correspondence: Pippa Scott, PhD, Institute of Social and Preventive Medicine, University of Bern, Finkenhubelweg 11, CH-3012 Bern, Switzerland. E-mail: firstname.lastname@example.org.
This project received funding from the World Health Organization and from the Swiss National Science Foundation (grant no. 138490). The authors have no other funding or conflicts of interest to disclose.
Supplemental digital content is available for this article. Direct URL citations appear in the printed text and are provided in the HTML and PDF versions of this article on the journal’s website (www.pidj.com).
Background: The optimal schedule and the need for a booster dose are unclear for Haemophilus influenzae type b (Hib) conjugate vaccines. We systematically reviewed relative effects of Hib vaccine schedules.
Methods: We searched 21 databases to May 2010 or June 2012 and selected randomized controlled trials or quasi-randomized controlled trials that compared different Hib schedules (3 primary doses with no booster dose [3p+0], 3p+1 and 2p+1) or different intervals in primary schedules and between primary and booster schedules. Outcomes were clinical efficacy, nasopharyngeal carriage and immunological response. Results were combined in random-effects meta-analysis.
Results: Twenty trials from 15 countries were included; 16 used vaccines conjugated to tetanus toxoid (polyribosylribitol phosphate conjugated to tetanus toxoid). No trials assessed clinical or carriage outcomes. Twenty trials examined immunological outcomes and found few relevant differences. Comparing polyribosylribitol phosphate conjugated to tetanus toxoid 3p+0 with 2p+0, there was no difference in seropositivity at the 1.0 μg/mL threshold by 6 months after the last primary dose (combined risk difference −0.02; 95% confidence interval: −0.10, 0.06). Only small differences were seen between schedules starting at different ages, with different intervals between primary doses, or with different intervals between primary and booster doses. Individuals receiving a booster were more likely to be seropositive than those at the same age who did not.
Conclusions: There is no clear evidence from trials that any 2p+1, 3p+0 or 3p+1 schedule of Hib conjugate vaccine is likely to provide better protection against Hib disease than other schedules. Until more data become available, scheduling is likely to be determined by epidemiological and programmatic considerations in individual settings.
Haemophilus influenzae type b (Hib) conjugate vaccines have led to large reductions in the incidence of invasive Hib disease, including meningitis and pneumonia, in countries that include them in their routine immunization schedule.1 Nevertheless, there are still more than 8 million cases of severe Hib disease worldwide annually in children under 5 years.2 Conjugate vaccines in use in 2012 contained Hib capsular polysaccharide (polyribosylribitol phosphate [PRP]) conjugated to the nontoxic CRM197 variant of diphtheria toxin (PRP-HbOC), meningococcal outer membrane protein (PRP-OMP), or most commonly tetanus toxoid (PRP-T).1
Countries are faced with decisions about optimal schedules for vaccines recommended for infants. The 2006 World Health Organization position paper on Hib conjugate vaccines states that a 3-dose schedule can be used with 1 to 2 months between doses, starting as young as 6 weeks.3 The position paper does not explicitly recommend a booster dose but states that if given it should be at 12–18 months of age. In 2012, most countries using Hib vaccine used a 3-dose primary schedule with no booster dose (3p+0 schedule). Some countries, mainly in Europe and the Americas, added a booster dose to the 3-dose primary schedule (3p+1 schedule) whereas other countries, mainly in Europe, used schedules with 2 primary doses and a booster (2p+1 schedule).4 Variation in Hib vaccination schedules reflects not only differences in the historical scheduling of childhood vaccines, setting-specific epidemiology, existing health service infrastructure and coadministered vaccines but also uncertainties about the optimal number of primary doses, the interval between doses in the primary schedule and the need for a booster dose.5 Whilst the clinical efficacy of Hib conjugate vaccines has been summarized,6–9 there have been no systematic reviews summarizing immunological, carriage and clinical outcomes from trials making head-to-head comparisons of different Hib vaccine schedules.
Here we systematically review the evidence from randomized controlled trials (RCTs) or quasi-randomized trials about the relative effects of 2p+0, 3p+0, 2p+1 and 3p+1 schedules and the effects of different timing of Hib conjugate vaccine doses.
The review process followed a protocol, which was completed before starting the review (Supplemental Digital Content 1, http://links.lww.com/INF/B612). Minor amendments were made after the review started, and these are recorded in the protocol document. We report here results for the head-to-head comparisons of Hib conjugate vaccine schedules described in the protocol. Comparisons of Hib schedules to no Hib vaccination will be reported elsewhere.
The literature search covered 21 electronic databases from the earliest citation until May 2010. There were 5 databases of published articles (AIM, Cochrane Library, LILACs, IndMED, Medline), 3 trial registries, 11 vaccine manufacturer databases and 2 regulatory authority websites. Search strategies included terms for “Hib” and “conjugate vaccine” adapted for each search engine (Supplemental Digital Content 2, http://links.lww.com/INF/B613). In June 2012, the Medline search was updated, using a filter to identify RCTs (2012 search only), and the AIM, CENTRAL, LILACs and IndMED searches were updated using the 2010 search strategy. Eligible trial registrations found in the 2010 search were also checked for new publications in June 2012.
Studies were considered eligible if they were randomized or quasi-randomized (eg, allocated according to date of birth) and examined children vaccinated with PRP-T, PRP-OMP or PRP-HbOC at less than 6 years of age. Trials were eligible if they assigned participants to the following comparisons: 3p+0 vs. 2p+0; 3p+0 vs. 2p+1; 3p+1 vs. 2p+1; 3p+1 vs. 3p+0. We also included studies that compared different intervals between doses and different ages at the start of the primary schedule. We excluded studies where both the schedule and the PRP-conjugated molecule differed between available comparison groups so that no comparisons within the trial assessed the effect of schedule differences alone.
Outcomes included invasive Hib disease as a combined outcome or separate diagnoses of Hib meningitis, pneumonia due to any cause, Hib pneumonia, epiglottitis, nasopharyngeal carriage of Hib, seropositivity after vaccination or geometric mean concentration (GMC) of PRP antibody. Seropositivity was defined by IgG antibody levels measured by enzyme-linked immunoassay or Farr-type radio-assay at threshold values of 0.15 and 1.0 μg/mL.10 Only systematically collected clinical outcomes were considered eligible.
Each title and abstract was screened for eligibility by 2 independent reviewers. The full texts of abstracts assessed by 1 or both reviewers to be potentially eligible were then screened for eligibility by 2 reviewers. Data were extracted on to a structured piloted form (available on request). Data were extracted by 2 independent reviewers, and differences were resolved by consensus. Items extracted included trial characteristics, outcomes, potential sources of heterogeneity and the risk of bias in individual trials.11 The risk of bias was assessed by examining trial features including the adequacy of random sequence generation, adequacy of allocation concealment, the use of outcome assessor blinding and the type of analysis.12,13 Analysis types included modified intention-to-treat (mITT) and per-protocol (PP). Modified intention-to-treat is used to describe analyses that included all randomized (or assigned) participants who had outcome data available with the possible exclusion of those who received no doses of vaccine, and PP is used to describe those that additionally excluded individuals with other protocol violations. We did not contact authors to obtain additional information.
We combined data statistically, where appropriate, using DerSimonian and Laird random-effects meta-analysis14 in STATA version 12 (StataCorp LP, College Station, TX). Between-trial heterogeneity was described using the I2 statistic, where values below 25% represent low heterogeneity, up to 50% moderate heterogeneity, up to 75% severe heterogeneity and more than 75% very severe heterogeneity.15 Where multiple intervention groups (or “trial arms”) were available within a trial to make a comparison of 2 schedules, we compared the groups that were most similar except for the difference in schedule. The decision about intervention groups to compare was made by 2 senior reviewers (N.L. and P.S.) without reference to trial results. For immunological outcomes, and for both the 1.0 and 0.15 ug/mL thresholds, we calculated the difference between groups in proportions seropositive (and 95% confidence intervals [CIs] using the normal approximation to the sampling distribution of the difference) and reported the risk difference as a proportion. A risk difference of 0.08 would indicate that an additional 8% of individuals in the first comparison group were seropositive than in the second comparison group (eg, 88% vs. 80%). Immunogenicity data were stratified according to the conjugated molecule (PRP-HbOC, -OMP or -T). We report 1.0 μg/mL threshold data in figures in preference to 0.15 μg/mL threshold data because risk differences were generally larger at the higher threshold. We report GMC data where seropositivity data were not available. We did not assess the presence of small trials biases using funnel plots or the Egger test because few trials were available for most analyses.
The literature searches yielded a total of 4337 unique items; 4032 items from the 2010 database and 305 from reference lists or repeat database searches. Of these, 4299 items were excluded (Fig. 1). The remaining 38 items referred to 20 randomized or quasi-randomized trials reporting on eligible comparisons and outcomes. Included studies are described in Table 1 and Supplemental Digital Content 3, http://links.lww.com/INF/B614.16–34 The 20 trials were conducted in 15 countries in Africa, Asia, Europe and North and South America. Sixteen trials used PRP-T, 3 used PRP-OMP and 2 used PRP-HbOC. One trial used PRP-T in 2 trial groups and PRP-HbOC in 2 other groups (Chile 1). Five trials did not report the number of individuals assigned to each intervention group. Where numbers were reported, a total of 6312 infants were assigned to intervention groups analyzed in this review: 661 infants to 2p+0 schedules, 1194 to 3p+0, 300 to 2p+1 and 4157 to 3p+1 schedules. The median number of participants in trials was 283 (range 54–1782).
Risk of Bias in Methods of Included Studies
Table 2 shows methodological features that could influence the risk of bias for the 20 trials. All trials individually assigned participants to intervention groups, and only 1 trial was judged to be quasi-randomized (USA 3). Allocation concealment was assessed as adequate in 2 trials and inadequate in 1 trial. In 17 trials, allocation concealment was not well enough described to be assessed. Outcome assessors (laboratory staff) were described as blinded in 11 of the 20 trials. Four trials reported mITT analyses (3 of which also conducted PP analyses but only stated that results were similar to mITT results), 9 reported PP analyses (2 of which also conducted mITT analyses but only stated that results were similar to PP results) and for 7 trials it was not clear which analysis was reported.
Head-to-head Comparisons Between Schedules
There were no eligible clinical or carriage outcome data from trials that compared different schedules of Hib vaccination. Twenty trials examined eligible schedule comparisons and presented seropositivity or GMC data. Nine of these provided data for comparisons of schedules with different numbers of doses in the primary or booster schedules and 14 of these provided data for comparisons of schedules with the same number of doses but different timings. Figures in Supplemental Digital Content 4 and 5, http://links.lww.com/INF/B615 and http://links.lww.com/INF/B616, show seropositivity (≥0.15 and ≥1.0 μg/mL) for all trial arms used in eligible comparative analyses.
Number of Doses in Primary and Booster Schedules, Immunological Data
3p+0 Versus 2p+0 Schedules.
Seven trials provided data for this comparison (Chile 1, Chile 2, Guatemala, Netherlands, Niger, Sweden, USA 2). Six examined PRP-T and 2 examined PRP-HbOC (1 trial examined both). Six trials reported seropositivity (Chile 1, Chile 2, Guatemala, Netherlands, Niger, Sweden), and all trials reported GMC data.
Figure 2 shows the risk difference (≥1.0 μg/mL) for seropositivity between groups receiving 3p+0 and 2p+0 schedules for trials where the interval between the last dose and blood draw was the same for both arms. In 3 trials, examining PRP-T (Chile 1, Niger, Sweden), neither the 2p nor the 3p schedule was consistently favored and heterogeneity was high (I2 90% at the 1.0 μg/mL threshold and 67% at the 0.15 μg/mL threshold, shortly after the last primary dose). By 6 months after the last primary dose, there was no difference between the schedules at the 1.0 μg/mL threshold (combined risk difference −0.02; 95% CI: −0.10, 0.06) and no heterogeneity (I2 0%). Heterogeneity remained high 6 months after the last primary dose at the 0.15 μg/mL threshold (I2 75%).
One trial (Chile 1) examined PRP-HbOC and presented seropositivity data. Point estimates favored the 3p group, but the confidence interval included the null effect. The trial which reported only GMC (USA 2) examined PRP-HbOC and compared a birth dose plus doses at 2 and 4 months of age with doses at 2 and 4 months of age. Two months after the last dose, the reported GMC in the 3p group (birth dose group) was 0.93 μg/mL (95% CI: 0.48, 1.69) and 0.20 μg/mL (95% CI: 0.10, 0.29) in the 2p group.
3p Versus 2p+1 Schedules.
One trial (Sweden) using PRP-T provided data for this comparison. At 13 months of age (7 months after the 3p group received their last primary dose and 1 month after the 2p+1 group received their booster), the risk difference was −0.79 (95% CI: −0.87, −0.71) at the 1.0 μg/mL threshold and −0.20 (95% CI: −0.27, −0.13) at 0.15 μg/mL, favoring the 2p+1 schedule.
3p+1 Versus 2p+1 Schedules.
Two trials using PRP-T provided data on seropositivity for this comparison (Netherlands, Sweden). Proportions seropositive 1 month after the booster vaccinations were high and similar in both groups. The combined risk difference was 0.01 (95% CI: −0.03, 0.05) at the 1.0 μg/mL threshold and 0.01 (95% CI: −0.01, 0.02) at 0.15 μg/mL with moderate (I2 56%) and low (I2 24%) heterogeneity, respectively.
3p+1 Versus 3p Schedules.
Two trials examined PRP-T for this comparison (Canada 2, Europe). One reported seropositivity data (Europe) and both reported GMC. At 13 months of age (1 month after the 3p+1 group received their booster dose), the 3p+1 schedule resulted in higher seropositivity than the 3p schedule at both the 1.0 µg/mL (risk difference 0.59, 95% CI: 0.52, 0.67) and 0.15 µg/mL thresholds (risk difference 0.16, 95% CI: 0.11, 0.22). One trial reported only GMC (Canada 2). Multiple intervention groups in this trial were available for comparison and not all are presented here. At 16 months of age, the intervention group that received a 3p schedule with a booster dose at 15 months of age achieved a GMC of 29.92 μg/mL (95% CI: 24.58, 36.43, Canada 2) and a group which had received a 3p schedule with no booster dose by 16 months of age achieved a GMC of 0.32 μg/mL (95% CI: 0.25, 0.41, Canada 2).
Age at Start of Primary Schedule, Immunological Data
Eight trials compared schedules with the same number of doses, in which the first dose was given earlier or later (Belgium, Chile 2, China 1, China 2, Gambia 1, Gambia 2, Netherlands, Turkey). Seven examined PRP-T, and 1 examined PRP-OMP (Gambia 1). Seven trials reported seropositivity data, and 8 reported GMC. Seropositivity results at the 1.0 µg/mL threshold are shown in Figure 3. Some schedule comparisons differed in both the age at first dose and in the interval between doses in the primary schedule. There were only small differences in seropositivity between schedules and heterogeneity was low. The combined risk difference 1 month after the last primary dose was 0.02 (95% CI: −0.01, 0.05) at the 1.0 μg/mL threshold, based on 3 trials (I2 1%). It was 0.01 (95% CI: 0.00, 0.02) at 0.15 μg/mL based on 4 trials (I2 0%).
The trial which reported only GMC (Gambia 2) compared PRP-T doses at 2 and 4 months to doses at 1 and 3 months of age. One month after the last dose of vaccine, the GMC was 0.41 μg/mL (95% CI: 0.28, 0.61) in infants receiving the first dose at 2 months and 0.26 μg/mL (95% CI: 0.19, 0.35) in the group with the earlier start. One study comparing a birth dose of PRP-HbOC plus doses at 2, 4 and 6 months of age with doses at 2, 4 and 6 months (USA 2) concluded that antibody levels were not higher after a birth dose.
Interval Between Doses, Immunological Data
Longer Versus Shorter Interval in Primary Schedules.
Five trials provided immunological data comparing longer and shorter intervals in the primary schedule (Belgium, France, Turkey, USA 1, USA 3). Four trials compared 2-month intervals with 1-month intervals (Belgium, France, Turkey, USA 3); 3 used 3p schedules to PRP-T and reported both seropositivity and GMC data (Belgium, France, Turkey) and 1 used a 2p schedule with PRP-OMP and reported GMC data only (USA 3). At the 1.0 µg/mL threshold, neither the 2-month nor the 1-month interval schedule was consistently favored, but results were heterogeneous (Fig. 4). At the 0.15 µg/mL threshold, no difference was seen between the schedules and heterogeneity was low: the combined risk difference 1 month after the last primary dose was 0.00 (95% CI: −0.02, 0.02), I2 0%. The trial using PRP-OMP (USA 3) was quasi-randomized, using alternation for assignment of interventions. The mean age at first vaccination was older in the 2-month interval group than in the 1-month interval group (4.1 and 3.2 months, respectively). Age-adjusted GMCs 1 month after the second vaccination were 3.95 μg/mL (95% CI: 2.63, 5.92) in the 2-month interval group and 2.32 μg/mL (95% CI: 1.48, 3.64) in the 1-month interval group. One trial compared 4-month intervals to 2-month intervals using PRP-OMP (USA 1), but results were difficult to interpret because the interval between vaccination and blood sampling differed between the groups being compared.
Longer Versus Shorter Interval Between Primary and Booster Schedules.
Seven trials examined PRP-T and provided seropositivity and GMC data (Canada 1, Canada 2, Canada 3, Chile 2, China 1, Europe, France). There were no differences in seropositivity 1 month after the booster dose and little between-study heterogeneity. The combined risk difference was 0.00 (95% CI: −0.01, 0.01) at the 1.0 μg/mL threshold (Fig. 5) and 0.00 (95% CI: −0.01, 0.01) at 0.15 μg/mL, with I2 14% and I2 0%, respectively.
Immunological data in this systematic review showed few differences that were both consistent and clinically relevant between Hib conjugate vaccine schedules with 2 or 3 primary doses or between schedules with different intervals between doses. Participants who had received booster doses were more likely to be seropositive than those of the same age who had not. There is an absence of clinical outcome or nasopharyngeal carriage data in head-to-head comparisons of Hib schedules.
This study is, to our knowledge, the first systematic review to examine the evidence from head-to-head comparisons of different Hib conjugate vaccine schedules. The wide search means that relevant RCTs are unlikely to have been missed. We also attempted a detailed assessment of potential sources of heterogeneity and bias, but many trials were not reported completely enough for the risk of bias to be assessed. A limitation identified by this review was the paucity of data on several outcomes and comparisons of interest. We did not include data from observational studies because well-conducted RCTs are at lower risk of bias than observational study designs,35,36 and because observational studies have been summarized elsewhere.37,38 The potential for bias does remain in many of the included trials, with allocation concealment, blinding of outcome assessors and exclusions after randomization being key trial design features influencing the risk of bias within trials.39 In particular, many trials in this review explicitly excluded some randomized individuals by conducting only a PP analysis. For some design features, it is difficult to categorize the risk of bias if the design feature is poorly described. For example, an incomplete description of allocation concealment could be compatible with either a high or low risk of bias; if allocation was adequate, the risk of bias is low but if allocation concealment was not well conducted, bias might occur if it can be easily predicted which individuals are more or less likely to seroconvert. Incomplete descriptions for features such as blinding are less important when considering immunological results where outcomes are assessed by laboratory technicians. It is possible and even likely that outcome assessors were blinded, even if this was not reported. Even if the laboratory staff are not blinded, automated procedures are likely to reduce the risk of bias.
The immunological data from available trials do not clearly favor either a 2-dose or a 3-dose primary schedule. There were also no important differences in seropositivity for PRP-T schedules starting at either 2 versus 3 months or PRP-OMP schedules starting at 1 versus 2 months of age. Available clinical data show good protection against invasive Hib disease with 2p+0 schedules using PRP-OMP,40 and with 3p+0 schedules using PRP-T or PRP-HbOC,40–44 when compared with no Hib vaccine, and these data have been summarized several times.6–9 However, estimates of vaccine efficacy from different trials cannot be compared directly as evidence of equivalence or superiority of 1 particular schedule, and there are too few trials for a network meta-analysis, which would allow such a comparison.45,46
Two-month intervals between doses in the primary schedule were not shown to be consistently more immunogenic than 1-month intervals. Meta-analyses either showed marked heterogeneity or showed little heterogeneity and no difference between 2- and 1-month intervals. It is challenging to draw conclusions about clinical efficacy based on immunological findings because the clinical relevance of Hib seropositivity levels and GMCs are not well established in general,10 and also because of differences in the schedules compared within each study other than the difference of interest. Data from an observational review found no strong evidence from cohort or case-control studies that the choice of intended intervals of 1 or 2 months between doses affects vaccine effectiveness,38 but differences between the intended and actual schedules and other factors such as herd immunity in the population again add complexity to interpretation.5
A booster dose after a primary series of either 2 or 3 doses of Hib conjugate vaccine results in high levels of seropositivity. There was no evidence from trials that the age at which the booster dose is given or the interval between the primary series and the booster dose affects the level of seropositivity. Seropositivity levels in children after a booster dose are much higher than in children who received the same primary schedule without a booster. The interval between the last vaccine dose and blood draw is, however, shorter in children receiving the booster than in those who received only the primary schedule, and it is not clear if differences in antibody levels can be interpreted as differences in protection from Hib disease.10 This review was not designed to collect data about antibody persistence, and therefore, caution should be taken when examining such data from this review. However, when data from individual groups in trials eligible for this review are plotted alongside each other (Figs., Supplemental Digital Content 4 and 5, http://links.lww.com/INF/B615 and http://links.lww.com/INF/B616), it can be seen that the proportion seropositive tends to be higher soon after a booster dose than soon after the last primary dose, or several months after the last primary dose, particularly at the 1.0 μg/mL threshold. Trials that assessed seropositivity more than 1 month after the last primary dose showed generally lower proportions seropositive than those assessing seropositivity 1 month after the last primary dose. In the 1 trial with long follow up after a booster dose, a high proportion of individuals remained seropositive at the 0.15 μg/mL threshold years after the booster dose and a much lower proportion at the 1.0 μg/mL threshold. These trends are in general agreement with studies that have found sustained antibody persistence after a booster dose.47,48 The United Kingdom experienced an increase in Hib cases several years after an initial decline in cases subsequent to the introduction of a 3p+0 schedule (2, 3, 4 months) alongside an early catch-up campaign. Cases again declined after 2 booster campaigns and the introduction of a routine booster dose to the vaccine schedule.49 However, the situations in which a booster dose should be used remain unclear and might relate to local epidemiology, coadministered vaccines and the potential for natural boosting as well as other factors.50,51
This review did not aim to examine the effects of coadministrated vaccines on Hib conjugate vaccine efficacy, which is best examined in trials comparing groups with different coadministered vaccines but with the same schedule. However, conclusions from our review about the relative effects of different schedules do not change when restricted to trials that coadministered acellular pertussis vaccine or trials that coadministered whole-cell pertussis vaccine. In analyses that included both trials in which whole-cell pertussis vaccine was coadministered and trials in which acellular pertussis vaccine was coadministered, the relative effects of different schedules of Hib vaccine did not appear to change substantially between studies. However, owing to the limited availability of data in each analysis, this could not be formally assessed using statistical methods such as meta-regression. The observational review conducted simultaneously with our review found no strong evidence from cohort studies that coadministration with acellular pertussis vaccine–reduced vaccine effectiveness, but 2 case-control studies conducted in the United Kingdom provided some evidence of a reduction.38,51,52 Further carefully conducted systematic reviews of RCTs, as well as observational data, could provide useful information about this and other questions about Hib vaccine scheduling.
Hib conjugate vaccine 2p+1, 3p+0 and 3p+1 schedules are all likely to provide protection against Hib disease and, until further data about the relative effects of different Hib vaccine schedules are available, the choice of schedule is likely to depend on the setting. For example, in settings where the burden of severe Hib disease lies with children under 1 year of age, it might be more appropriate to provide 3 doses of Hib vaccine early in life. In settings where the disease burden occurs later, or where a resurgence of Hib cases is seen after the introduction of Hib vaccine, it might be advantageous to use a schedule where the third dose is given as a booster. Programmatic considerations are also likely to influence the choice of Hib vaccine schedule. Costs of vaccine administration are likely to be lower and vaccine coverage higher if vaccine administration is combined with other routine scheduled health visits. Additionally, most Hib vaccines are administered as combined vaccines, which means that the scheduling of the other coadministered vaccines must also taken into account when choosing a Hib vaccine schedule.
Future decisions relating to Hib vaccination could be informed by well-conducted RCTs with head-to-head comparisons of schedules that collect data on clinical outcomes. Trials comparing schedules would need to be extremely large to provide sufficient statistical power to show difference between schedules, but trials of this type have been conducted for other vaccines.53
Variation in the burden of disease, health infrastructure and scheduling of other vaccines creates complexity in determining optimal vaccination schedules. Thus, information on the benefits of different vaccine schedules is essential if informed decisions are to be made. In this comprehensive systematic review, we highlight the absence of clinical and carriage data from trials comparing Hib vaccine schedules and scarce immunological data from such comparisons. We show there is no clear evidence from vaccine trials that any 2p+1, 3p+0 or 3p+1 schedule of Hib conjugate vaccine is likely to provide better protection against Hib disease than other schedules. Until additional data about the relative effects of different Hib vaccine schedules are available, the choice of Hib vaccination schedule is likely to be determined by the epidemiological and programmatic conditions in individual settings.
We thank the WHO secretariat and participants at expert meetings at WHO for their input, discussion and comments on this review. We also thank the World Health Organization and the Swiss National Science Foundation (grant no. 138490) for funding this project.
1. Morris SK, Moss WJ, Halsey N. Haemophilus influenzae type b conjugate vaccine use and effectiveness. Lancet Infect Dis. 2008;8:435–443
2. Watt JP, Wolfson LJ, O’Brien KL, et al.Hib and Pneumococcal Global Burden of Disease Study Team. Burden of disease caused by Haemophilus influenzae type b in children younger than 5 years: global estimates. Lancet. 2009;374:903–911
3. World Health Organization. . WHO position paper on Haemophilus influenzae type b conjugate vaccines. Wkly Epidemiol Rec. 2006;81:445–452
5. Fitzwater SP, Watt JP, Levine OS, et al. Haemophilus influenzae type b conjugate vaccines: considerations for vaccination schedules and implications for developing countries. Hum Vaccin. 2010;6:810–818
6. Swingler G, Fransman D, Hussey G. Conjugate vaccines for preventing Haemophilus influenzae type B infections. Cochrane Database Syst Rev. 2007:CD001729
7. Obonyo CO, Lau J. Efficacy of Haemophilus influenzae type b vaccination of children: a meta-analysis. Eur J Clin Microbiol Infect Dis. 2006;25:90–97
8. Griffiths UK, Clark A, Gessner B, et al. Dose-specific efficacy of Haemophilus influenzae type b conjugate vaccines: a systematic review and meta-analysis of controlled clinical trials. Epidemiol Infect. 2012;140:1343–1355
9. Theodoratou E, Johnson S, Jhass A, et al. The effect of Haemophilus influenzae type b and pneumococcal conjugate vaccines on childhood pneumonia incidence, severe morbidity and mortality. Int J Epidemiol. 2010;39(suppl 1):i172–i185
11. Jüni P, Altman DG, Egger M. Systematic reviews in health care: Assessing the quality of controlled clinical trials. BMJ. 2001;323:42–46
12. Nüesch E, Trelle S, Reichenbach S, et al. The effects of excluding patients from the analysis in randomised controlled trials: meta-epidemiological study. BMJ. 2009;339:b3244
13. Nüesch E, Reichenbach S, Trelle S, et al. The importance of allocation concealment and patient blinding in osteoarthritis trials: a meta-epidemiologic study. Arthritis Rheum. 2009;61:1633–1641
14. DerSimonian R, Laird N. Meta-analysis in clinical trials. Control Clin Trials. 1986;7:177–188
15. Higgins JP, Thompson SG. Quantifying heterogeneity in a meta-analysis. Stat Med. 2002;21:1539–1558
16. Hoppenbrouwers K, Kanra G, Roelants M, et al. Priming effect, immunogenicity and safety of an Haemophilus influenzae type b-tetanus toxoid conjugate (PRP-T) and diphtheria-tetanus-acellular pertussis (DTaP) combination vaccine administered to infants in Belgium and Turkey. Vaccine. 1999;17:875–886
17. Scheifele DW, Guasparini R, Lavigne P. A comparative study of PENTA vaccine booster doses given at 12, 15, or 18 months of age. Vaccine. 1999;17:543–550
18. Scheifele DW, Halperin SA, Rubin E, et al. Safety and immunogenicity of a pentavalent combination vaccine (diphtheria, tetanus, acellular pertussis, polio, and haemophilus influenzae type B conjugate) when administered as a fourth dose at 15 to 18 months of age. Hum Vaccin. 2005;1:180–186
19. Scheifele DW, Halperin SA, Ochnio JJ, et al. Immunologic considerations for the timing of the booster dose of 7-valent pneumococcal conjugate vaccine in young children. Pediatr Infect Dis J. 2007;26:387–392
20. Lagos R, Valenzuela MT, Levine OS, et al. Economisation of vaccination against Haemophilus influenzae type b: a randomised trial of immunogenicity of fractional-dose and two-dose regimens. Lancet. 1998;351:1472–1476
21. Lagos R, Kotloff K, Hoffenbach A, et al. Clinical acceptability and immunogenicity of a pentavalent parenteral combination vaccine containing diphtheria, tetanus, acellular pertussis, inactivated poliomyelitis and Haemophilus influenzae type b conjugate antigens in two-, four- and six-month-old Chilean infants. Pediatr Infect Dis J. 1998;17:294–304
22. Li RC, Li FX, Li YP, et al. Antibody persistence at 18–20 months of age and safety and immunogenicity of a booster dose of a combined DTaP-IPV//PRP approximately T vaccine compared to separate vaccines (DTaP, PRP approximately T and IPV) following primary vaccination of healthy infants in the People’s Republic of China. Vaccine. 2011;29:9337–9344
23. GlaxoSmithKline. Immunogenicity and safety of GlaxoSmithKline Biologicals’ DTPa-IPV/Hib (Infanrix-IPV+Hib™) in infants. Results summary for study ID 112584. Available at: http://www.gsk-clinicalstudyregister.com
. Accessed January 24, 2013
24. Knuf M, Pantazi-Chatzikonstantinou A, Pfletschinger U, et al. An investigational tetravalent meningococcal serogroups A, C, W-135 and Y-tetanus toxoid conjugate vaccine co-administered with Infanrix™ hexa is immunogenic, with an acceptable safety profile in 12-23-month-old children. Vaccine. 2011;29:4264–4273
26. Campbell H, Byass P, Ahonkhai VI, et al. Serologic responses to an Haemophilus influenzae type b polysaccharide-Neisseria meningitidis outer membrane protein conjugate vaccine in very young Gambian infants. Pediatrics. 1990;86:102–107
27. Mulholland EK, Byass P, Campbell H, et al. The immunogenicity and safety of Haemophilus influenzae type b-tetanus toxoid conjugate vaccine in Gambian infants. Ann Trop Paediatr. 1994;14:183–188
28. Asturias EJ, Mayorga C, Caffaro C, et al. Differences in the immune response to hepatitis B and Haemophilus influenzae type b vaccines in Guatemalan infants by ethnic group and nutritional status. Vaccine. 2009;27:3650–3654
29. Labadie J, Sundermann L, Rumke HThe DPT-IPV Hib vaccine study group. Multi-center study on the simultaneous administration of DPT-IPV and Hib PRP-T vaccines. Rijksinstituut voor Volksgezondheid en Milieu RIVM. 1996. Available at: http://www.rivm.nl/bibliotheek/rapporten/124001003.html
. Accessed January 24, 2013
30. Campagne G, Garba A, Schuchat A, et al. Response to conjugate Haemophilus influenzae B vaccine among infants in Niamey, Niger. Am J Trop Med Hyg. 1998;59:837–842
31. Carlsson RM, Claesson BA, Selstam U, et al. Safety and immunogenicity of a combined diphtheria-tetanus-acellular pertussis-inactivated polio vaccine-Haemophilus influenzae type b vaccine administered at 2-4-6-13 or 3-5-12 months of age. Pediatr Infect Dis J. 1998;17:1026–1033
32. Anderson EL, Decker MD, Englund JA, et al. Interchangeability of conjugated Haemophilus influenzae type b vaccines in infants. JAMA. 1995;273:849–853
33. Lieberman JM, Greenberg DP, Wong VK, et al. Effect of neonatal immunization with diphtheria and tetanus toxoids on antibody responses to Haemophilus influenzae type b conjugate vaccines. J Pediatr. 1995;126:198–205
34. Lenoir AA, Granoff PD, Granoff DM. Immunogenicity of Haemophilus influenzae type b polysaccharide-Neisseria meningitidis outer membrane protein conjugate vaccine in 2- to 6-month-old infants. Pediatrics. 1987;80:283–287
35. Schulz KF, Altman DG, Moher DCONSORT Group. . CONSORT 2010 statement: updated guidelines for reporting parallel group randomised trials. BMJ. 2010;340:c332
36. Sibbald B, Roland M. Understanding controlled trials. Why are randomised controlled trials important? BMJ. 1998;316:201
37. O’Loughlin RE, Edmond K, Mangtani P, et al. Methodology and measurement of the effectiveness of Haemophilus influenzae type b vaccine: systematic review. Vaccine. 2010;28:6128–6136
38. Jackson C, Mann A, Mangtani P, et al. Effectiveness of Haemophilus influenzae type b (Hib) vaccines administered according to different schedules: systematic review and meta-analysis of observational data. Pediatr Infect Dis J. 2013;32:1261–1269
39. Schulz KF, Chalmers I, Hayes RJ, et al. Empirical evidence of bias. Dimensions of methodological quality associated with estimates of treatment effects in controlled trials. JAMA. 1995;273:408–412
40. Santosham M, Wolff M, Reid R, et al. The efficacy in Navajo infants of a conjugate vaccine consisting of Haemophilus influenzae type b polysaccharide and Neisseria meningitidis outer-membrane protein complex. N Engl J Med. 1991;324:1767–1772
41. Lagos R, Horwitz I, Toro J, et al. Large scale, postlicensure, selective vaccination of Chilean infants with PRP-T conjugate vaccine: practicality and effectiveness in preventing invasive Haemophilus influenzae type b infections. Pediatr Infect Dis J. 1996;15:216–222
42. Mulholland K, Hilton S, Adegbola R, et al. Randomised trial of Haemophilus influenzae type-b tetanus protein conjugate vaccine [corrected] for prevention of pneumonia and meningitis in Gambian infants. Lancet. 1997;349:1191–1197
43. Gessner BD, Sutanto A, Linehan M, et al. Incidences of vaccine-preventable Haemophilus influenzae type b pneumonia and meningitis in Indonesian children: hamlet-randomised vaccine-probe trial. Lancet. 2005;365:43–52
44. Black SB, Shinefield HR, Fireman B, et al. Efficacy in infancy of oligosaccharide conjugate Haemophilus influenzae type b (HbOC) vaccine in a United States population of 61,080 children. The Northern California Kaiser Permanente Vaccine Study Center Pediatrics Group. Pediatr Infect Dis J. 1991;10:97–104
45. Higgins JP, Whitehead A. Borrowing strength from external trials in a meta-analysis. Stat Med. 1996;15:2733–2749
46. Lu G, Ades AE. Combination of direct and indirect evidence in mixed treatment comparisons. Stat Med. 2004;23:3105–3124
47. Borrow R, Andrews N, Findlow H, et al. Kinetics of antibody persistence following administration of a combination meningococcal serogroup C and haemophilus influenzae type b conjugate vaccine in healthy infants in the United Kingdom primed with a monovalent meningococcal serogroup C vaccine. Clin Vaccine Immunol. 2010;17:154–159
48. Southern J, McVernon J, Gelb D, et al. Immunogenicity of a fourth dose of Haemophilus influenzae type b (Hib) conjugate vaccine and antibody persistence in young children from the United Kingdom who were primed with acellular or whole-cell pertussis component-containing Hib combinations in infancy. Clin Vaccine Immunol. 2007;14:1328–1333
49. Ladhani S, Slack MP, Heys M, et al. Fall in Haemophilus influenzae serotype b (Hib) disease following implementation of a booster campaign. Arch Dis Child. 2008;93:665–669
50. Slack MP, Azzopardi HJ, Hargreaves RM, et al. Enhanced surveillance of invasive Haemophilus influenzae disease in England, 1990 to 1996: impact of conjugate vaccines. Pediatr Infect Dis J. 1998;17(suppl 9):S204–S207
51. McVernon J, Andrews N, Slack MP, et al. Risk of vaccine failure after Haemophilus influenzae type b (Hib) combination vaccines with acellular pertussis. Lancet. 2003;361:1521–1523
52. McVernon J, Andrews N, Slack M, et al. Host and environmental factors associated with Hib in England, 1998–2002. Arch Dis Child. 2008;93:670–675
53. Palmu AA, Jokinen J, Borys D, et al. Effectiveness of the ten-valent pneumococcal Haemophilus influenzae protein D conjugate vaccine (PHiD-CV10) against invasive pneumococcal disease: a cluster randomised trial. Lancet. 2013;381:214–222
Haemophilus influenzae type b conjugate vaccine; vaccine schedules; systematic review; meta-analysis
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