Probiotics, prebiotics infant formula use in preterm or low birth weight infants: a systematic review

Abstract

Background

Previous reviews (2005 to 2009) on preterm infants given probiotics or prebiotics with breast milk or mixed feeds focused on prevention of Necrotizing Enterocolitis, sepsis and diarrhea. This review assessed if probiotics, prebiotics led to improved growth and clinical outcomes in formula fed preterm infants.

Methods

Cochrane methodology was followed using randomized controlled trials (RCTs) which compared preterm formula containing probiotic(s) or prebiotic(s) to conventional preterm formula in preterm infants. The mean difference (MD) and corresponding 95% confidence intervals (CI) were reported for continuous outcomes, risk ratio (RR) and corresponding 95% CI for dichotomous outcomes. Heterogeneity was assessed by visual inspection of forest plots and a chi² test. An I² test assessed inconsistencies across studies. I²> 50% represented substantial heterogeneity.

Results

Four probiotics studies (N=212), 4 prebiotics studies (N=126) were included. Probiotics: There were no significant differences in weight gain (MD 1.96, 95% CI: -2.64 to 6.56, 2 studies, n=34) or in maximal enteral feed (MD 35.20, 95% CI: -7.61 to 78.02, 2 studies, n=34), number of stools per day increased significantly in probiotic group (MD 1.60, 95% CI: 1.20 to 2.00, 1 study, n=20). Prebiotics: Galacto-oligosaccharide / Fructo-oligosaccharide (GOS/FOS) yielded no significant difference in weight gain (MD 0.04, 95% CI: -2.65 to 2.73, 2 studies, n=50), GOS/FOS yielded no significant differences in length gain (MD 0.01, 95% CI: -0.03 to 0.04, 2 studies, n=50). There were no significant differences in head growth (MD −0.01, 95% CI: -0.02 to 0.00, 2 studies, n=76) or age at full enteral feed (MD −0.79, 95% CI: -2.20 to 0.61, 2 studies, n=86). Stool frequency increased significantly in prebiotic group (MD 0.80, 95% CI: 0.48 to 1.1, 2 studies, n=86). GOS/FOS and FOS yielded higher bifidobacteria counts in prebiotics group (MD 2.10, 95% CI: 0.96 to 3.24, n=27) and (MD 0.48, 95% CI: 0.28 to 0.68, n=56).

Conclusions

There is not enough evidence to state that supplementation with probiotics or prebiotics results in improved growth and clinical outcomes in exclusively formula fed preterm infants.

Background

Growth is a major challenge for premature and low birth weight infants (born < 37 weeks gestation or with a birth weight of < 2500 g). They have several factors that put them at risk for nutritional deficiencies resulting in poor growth. Decreased nutrient stores result in low body stores of glycogen, fat, protein, fat soluble vitamins, calcium, phosphorus, magnesium and trace minerals. Preterm infants require increased energy and nutrients for rapid growth and may need a 10 fold increase in weight gain in order to achieve optimum catch up growth [1, 2]. To achieve optimum growth for the preterm infant, the goals are to continue the process of intra-uterine growth in an extra-uterine environment until 40 weeks post conception, foster catch-up growth and nutrient accumulation in the post discharge period [3–6]. A weight gain of 15 to 20 g/ kg/day, length of 0.75 to 1.0 cm/week and head circumference 0.75 cm/week is required. This is difficult to achieve and requires between 130 – 135 kcal / kg /day to maintain this growth rate [3]. Furthermore, infants lose weight after birth (up to 6% to 8% for extreme low birth weight infants) and they often do not regain the weight for up to 1 to 2 weeks [5]. Daily growth monitoring (weight gain, linear and head circumference) then becomes vital.

Preterm infants have immature physiological systems due to an underdeveloped gastrointestinal barrier function as reflected by increased intestinal permeability. As a result, potentially pathogenic bacteria translocate from the intestinal lumen and cause systemic infections [7]. Reducing intestinal permeability is associated with gut maturation which promotes growth and avoids severe infections [4]. In addition, digestive and absorptive capabilities are decreased due to low concentration of lactase, pancreatic lipase and bile salts. Gastrointestinal motility and stomach capacity are decreased which limits feeding volume and gastric emptying. A coordinated suck and swallow is not developed until 32 to 34 weeks gestation. Introduction of enteral feeding maybe delayed due to increased risk of aspiration [1, 2, 8, 9]. Preterm infants in neonatal intensive care units (NICUs) develop a different intestinal microbiota compared to healthy breast fed infants. This is due to decreased exposure to the maternal microbiota, increased exposure to organisms that colonize NICUs, multiple courses of antibiotics and delays in feeding [8, 9].

Humans have consumed probiotics in the form of fermented food, dairy products and more recently infant and toddler formula. Probiotics are defined as “live microorganisms” which when administered in adequate amounts confer a health benefit to the host [10]. The main probiotic organisms used worldwide belong to the genera Lactobacillus and Bifidobacteria and are found in the gastrointestinal micro flora [10, 11]. Prebiotics are found in fruit and vegetable components, they are non- digestible food ingredients that benefit the host by selectively stimulating the growth and/or activity of one or a limited number of bacteria in the colon and improving the host’s health [12, 13]. The most widely studied prebiotics are inulin, fructo-oligosaccharide (FOS) and galacto-oligosaccharide (GOS) which are plant storage carbohydrates in vegetables, cereals and fruit. FOS and inulin are added to different foods as fat and sugar replacements to improve texture or for their functional benefits [12, 14–16]. Probiotics and prebiotics are added to infant formula to promote an intestinal microbiota resembling that of breastfed infants which have a greater concentration of bifidobacteria and less pathogenic bacteria than formula fed infants [10, 17].

There are a number of ways in which probiotics improve health. Health benefits conferred by probiotic bacteria are strain specific and not species or genus specific [10]. Probiotic bacteria improve health by affecting the immune system in different ways. They increase cytokine production such as Interleukin-6 (IL-6), Interferon- gamma (IFN-γ), Tissue Necrosis Factor – alpha (TNF-α), Interleukin-1beta (IL-1β) and Interleukin-10 (IL-10) [18]. Some strains increase phagocytic activity of peripheral blood leukocytes (monocytes, polymorphonuclear cells). Other strains strengthen the mucosal barrier function by promoting the production of mucosal antibodies and reducing the trans mucosal transfer of antigens. This reduces the intestinal permeability which in turn promotes growth [19–22]. Probiotics bacteria also enhance production of low molecular weight antibacterial substances produced by epithelial cells and production of short chain fatty acids, the main energy source for colonocytes. This maintains the integrity of colon mucosa [19, 23–26].

Prebiotics are resistant to digestive enzymes and pH extremes found in the human gastrointestinal tract. They transit through the upper gastrointestinal tract and reach the colon intact where they are selectively fermented by indigenous bacteria, especially bifidobacteria and lactobacilli [12, 15, 26, 27]. Beneficial bacteria (including bifidobacteria and lactobacilli) possess enzymes needed to metabolize prebiotics, while other bacteria (such as E coli, clostridia and salmonella) do not [15, 27]. Consumption of prebiotics by preterm formula fed infants results in an increase of beneficial microorganisms in the colon, decreasing harmful bacteria to the levels found in breastfed infants. This improves the gastrointestinal mucosal barrier (decreasing intestinal permeability) which prevents infections and eventually results in improved growth [27, 28]. In general the aim of adding probiotics and prebiotics to preterm infant formula is to improve growth, development and decrease infections by promoting an intestinal microbiota resembling that of breastfed infants [9, 29, 30].

The effects of probiotics on the intestinal microbiota of premature infants have been varied due to differences on gestational age and products administered. Effects of probiotics on weight gain have also been varied. Administration of Bifidobacteria breve led to improved weight gain while Saccharomyces bourladii did not [9]. With premature infants optimal strains and dose regimens are yet to be examined closely [8]. The effects of prebiotics on the growth of premature infants are not clear. If prebiotic supplementation reduces the risk of Necrotizing Enterocolitis (NEC) or improves feed tolerance in very low birth weight infants is yet to be established [8, 9]. Recent systematic reviews (published from 2005 to 2009) on the use of probiotics or prebiotics in preterm infants have focused on prevention of NEC and / or sepsis, impact on diarrhea [31–34]. These reviews focused on studies that used breast milk and mixed feeds (formula combined with breast milk). This review included infants given only infant formula and focused on growth with clinical outcomes that were not adequately addressed by previous reviews.

The Human Research Ethics Committee at the University of Stellenbosch, South Africa reviewed the review protocol (unpublished), ruled that all data to be collected for this review was from the public domain and was therefore exempt from ethical approval.

Objective

To assess if addition of probiotics or prebiotics to preterm infant formula led to improved growth and clinical outcomes in preterm or low birth weight infants.

Methods

Eligibility criteria

All randomized controlled trials (RCTs), irrespective of language, which compared the use of preterm infant formula containing probiotic(s) or prebiotic(s) to conventional preterm infant formula without or with placebo amongst preterm infants born <37 weeks gestation, low birth weight infants with <2.5 kg at birth and hospitalized, receiving formula feeds and / or parenteral feed were considered. Studies published as abstracts were included if sufficient information could be obtained to assess study quality and obtain relevant study findings.

Outcome measurements

Primary outcomes included: Short term growth parameters (assessed for entire study duration approximately 4 weeks): weight gain (grams/day or grams/week), linear growth (centimeters/week), head growth (cm/week). Secondary outcomes included: Complications: Incidence of NEC (defined as suspected or confirmed positive Bell stage II or more), Sepsis (defined as signs or symptoms of infection and positive blood culture), Other infections (example bacteraemia defined as blood cultured positive for bacteria), Mortality / death. Adverse events during entire study duration: Number of days on parenteral, number of days to full enteral nutrition, maximal enteral feed (millilitres/day, millilitres/kilogram/day, millilitres /kilogram). Feed intolerance: Incidence of vomiting, gastric aspirates, abdominal distension. Stool characteristics: Stooling frequency and stool consistency as firm, loose or watery. Changes in intestinal permeability as measured by ratio of Lactulose / mannitol in urine or other sugar absorption tests (such as lactulose / L – rhamnose ratio, D- xylose, 3-O2- methyl-D- glucose tests). Gastrointestinal (GI) micro flora: number of colony forming units (cfu) of bifidobacteria, lactobacillus and pathogens post intervention).

Search method for identification of studies

A literature search in all languages was conducted on electronic databases which included The Cochrane Central Register for Controlled Trials 2009, Scopus (1990 to 19/01/2010), EBSCO host (1960 to 15/11/2009), OVID (1950 to 01/12/2009), SPORT Discus (1960 to 19/01/2010), Web of Science (1970 to 19/01/2010), Science Direct (1950 to 30/11/2009), EMBASE (1980 to 01/12/2009), CINAHL (1981 to 19/01/2010), PUBMED / MEDLINE (1966 to 10/04/2010), Latin American Caribbean Health Sciences literature (LILACS), (1965 to 19/01/2010), NLM Gateway (1950–1966). RCTs published in non-English language journals were translated by independent translators who were familiar with the subject matter. The search strategy used to search PUBMED is shown on Table 1. This search strategy was modified to search other electronic databases.

Table 1 Search strategy used in PUBMED

We conducted a hand search on abstracts of major conference proceedings such as the Pediatric Academic Society meetings (www.pas-meetings.org, www.abstracts2view.com), cross checked references cited in RCTs and in recent reviews (published from 2005 to 2009) for additional studies not identified by electronic searches and specialty journals which were not included in any database such as Pediatrika, Chinese Journal of Microecology and International Journal of Probiotics and Prebiotics.

To identify on-going and unpublished trials, we contacted experts in the field, manufacturers of infant formula containing probiotics and prebiotics, we searched web sites of companies that have conducted or were conducting RCTs on probiotics and prebiotics e.g. Pfizer (www.pfizerpro.com/clinicaltrials), Chris Hansen Laboratory (www.chr-hansen.com/research_development/documentation.html). We also searched prospective trial registries such as World Health Organisation (WHO) International Clinical Trials Registry Platform Search Portal (www.who.int/trialsearch), Clinical Trials.gov register (www.clinicaltrials.gov), Current Controlled Trials metaRegister of Controlled Trials [mRCT] (www.controlled-trials.com/mrct) and www.clinicaltrialresults.org.

Selection of studies

Two reviewers (MM, ML) independently reviewed all abstracts, citations and identified potentially eligible studies. The full reports of eligible studies were retrieved by one reviewer (MM) and the pre-specified selection criteria applied independently by two reviewers (MM, ML) using a study eligibility form. (Figure 1) If more than one publication of a study existed, all reports of the study were grouped together under one study name. Any disagreements between the reviewers were resolved through discussion. If disagreements could not be resolved a third party was consulted. Trial authors were contacted if eligibility was unclear.

Figure 1

Study eligibility form.

Assessment of quality of evidence

Two reviewers (MM, ML) independently assessed the risk of bias of included studies as described in the Cochrane Handbook for Systematic Reviews for Interventions according to the following 6 components. 1) sequence generation; 2) allocation concealment; 3) blinding; 4) incomplete outcome data; 5) selective outcome reporting; and 6) other sources of bias [35]. Where necessary, trial authors were contacted for clarification on the methodology of their studies. Any disagreements regarding risk of bias were resolved through discussion between MM, ML and RB.

Data extraction and management

Two reviewers (MM, ML) independently extracted data using a pre tested data extraction form. The reviewers (MM, ML) cross checked data and resolved any differences through discussion. One reviewer (MM) entered the data in Review Manager (RevMan 5) and the other reviewer (ML) validated the data. Trial authors were contacted for missing data or for clarification.

Data synthesis and management

Results for probiotic and prebiotic studies were analysed separately. For continuous outcomes the mean difference (MD) and corresponding 95% confidence intervals (CI) were calculated. For dichotomous outcomes, the risk ratio (RR) and corresponding 95% CI were calculated. Trial authors were contacted if there was missing data in their reports. Available case analysis was used where there was missing data. The potential impact of the missing data on the results of the review is addressed in the discussion section. Heterogeneity of the trials used in the review was assessed by visually inspecting the forest plots to detect overlapping confidence intervals and by performing a chi² test. A p<0.1 was considered statistically significant. An I-square test (I²) was used to test for inconsistencies across studies. If the I² exceeded 50% and visual inspection of the forest plot supported these results, this represented substantial heterogeneity.

If the included studies were not clinically diverse and had similar outcome measures, a Meta - analysis was carried out in Review Manager software (RevMan 5) by one review author (AM). For continuous data, if heterogeneity was low, an inverse variance fixed-effect method was used. If heterogeneity was high, an inverse variance random-effects method was used. For dichotomous data, if heterogeneity was low, a Mantel-Haenszel fixed-effects method was used. If heterogeneity was high, a Mantel- Haenszel random-effects method was used. The source of heterogeneity was explored through subgroup analysis with respect to the type of intervention. If studies were too diverse, no Meta-analysis was conducted and a narrative synthesis was provided. We had intended to perform sensitivity analysis with respect to study quality in order to investigate the robustness of our findings but this could not be done mainly because most of the meta-analysis had too few studies (mostly two) to warrant sensitivity analysis. In some cases, all the studies in the meta-analysis had similar study quality thus rendering sensitivity analysis inappropriate.

Results

Results of the search and description of studies

Electronic search of available databases yielded 151 citations. After reading titles, abstracts, the duplicate reports were removed and 35 potentially relevant articles were identified. A hand search yielded 4 more articles. The full text reports were retrieved and reviewed for eligibility. One study was published in two other reports. The three studies were considered as one study since they reported the same identical study and are referred to as Boehm 2002 in this review [36–38]. Eight published studies (four probiotic and four prebiotic studies) [36, 39–45] and five on-going studies were included in this review [46–51]. The process followed is shown in Figure 2. Table 2 gives a list of 27 studies which were excluded for: use of breast milk or mixed feeds (18 studies), no use of probiotic or prebiotic (2 studies), being a follow –up study, not RCT (3 studies), duplicate publishing (1 study); using different inclusion criteria with different outcomes (2 studies) and type of feed was unspecified (1 study). No eligible studies were excluded for failure to report the review’s pre-specified outcomes.

Figure 2

Process followed in the selection of studies.

Table 2 Excluded studies with reasons for exclusion

A summary of the included probiotic, prebiotic and on-going studies are shown in Tables 3, 4 and 5. The included probiotic studies (N=212) were conducted in Greece, Italy and United States of America (USA). Treatment duration was 30 days using different probiotics. All four probiotic studies reported short term growth parameters (weight gain) which were recorded daily during the entire study duration [Table 3]. None of the probiotic studies reported data on: other types of infections, use of parenteral nutrition, feed intolerance (gastric aspirate [ml], abdominal distension) and stool consistency. The included prebiotic studies (N=126) were conducted in conducted in Greece, Italy, and Germany. Treatment duration ranged from 14 days to 28 days. All four prebiotic studies reported short term growth parameters (weight gain, length, head growth) which were recorded at different intervals during the entire study duration [Table 4]. None of the prebiotic studies reported data on: complications (NEC, sepsis, other types of infections, death / mortality), use of parenteral nutrition, feed intolerance (vomiting, gastric aspirate [ml], abdominal distension) and changes in intestinal permeability.

Table 3 A summary of four included probiotic studies

Table 4 A summary of four included prebiotic studies

Table 5 A summary of five on-going studies

Risk of bias

The quality of the included studies was assessed across six domains using guidelines from the Cochrane Handbook for Systematic Reviews of Interventions [35] (Figure 3).

Figure 3

Methodological quality of included studies.

Random sequence generation: Three trials described clearly the methods used for random sequence generation [40, 41, 44]. Mihatsch used computer generated random lists with variable block sizes [44]. Stratiki used balance block randomization using random numbers [40] and Reuman used random numbers list combined with the last digit of the patients’ medical record [41]. The method used for random sequence generation was not clearly described 5 studies [36, 39, 42, 43, 45].

Allocation Concealment: In two trials treatment allocation was adequately concealed [33, 40]. In the Stratiki trial, treatment allocation was conducted by a third party who was not involved in the study (Nutritional service) [40]. Mihatsch used precoded sachets in sealed envelopes [44]. In one study treatment allocation was not adequately concealed because the method used was alternation, matching of infants by birth weight and gestational age [41]. In the rest of the studies, allocation concealment was not clearly demonstrated or described [36, 39, 42, 43].

Blinding: Blinding of study participants, care providers and assessors was clearly done in 4 trials [39–41, 44]. In the other 4 trials, there was not enough information given on the blinding method to make a judgement [36, 42, 43, 45].

Incomplete outcome data: Reported outcome data was satisfactory for all the eight included studies. Five studies had no missing outcome data [36, 41–44]. In other three studies, the missing outcome data was balanced across the intervention groups with similar reasons reported [39, 40, 45].

Selective reporting (reporting bias): In all eight studies, the pre-specified outcomes in the methods section were reported in the results section [36, 39–45].

Other potential sources of bias: Only one trial had a baseline imbalance which was a potential source of bias. Costalos had 51 infants enrolled in the treatment group and 36 infants in the placebo group. No explanation was presented whether the imbalance was due to a problem at randomization stage [39]. All other studies appeared to be free from other potential sources of bias.

Effects of interventions

Probiotics versus control

Four studies investigated the effect of probiotic administration versus no probiotic (control group) [39–42].

Primary outcomes: short term growth parameters

Weight gain

All four studies reported on weight gain [39–42]. Results from two studies (n=34) were pooled in a meta-analysis [41, 42]. There was no statistically significant difference in weight gain (g/day) between the probiotic and control groups (MD 1.96, 95% CI: -2.64 to 6.56). No statistically significant heterogeneity was observed (Chi²=0.18, p=0.67, I²=0%) (Figure 4)

Figure 4

Effect of probiotic administration on weight gain (g/day).

Two studies [39, 40] reported their results using medians and could not be pooled in a meta - analysis. Costalos 2003 reported no statistically significant difference in weight gain (g/week) between the probiotic and control groups (p>0.05) [median (Interquartile range) of 163.5 (17.7) for the probiotic group (n=51) compared to 155.8 (16.5) for the control group (n=36)] [39]. Stratiki 2007 also reported no statistically significant difference in weight gain (g/day) between the probiotic and control groups (p=0.144) [median (range) of 28.3 (12 to 38) for the probiotic group (n=41) compared to 30 (10 to 40) for the control group (n=34)] [40].

Linear growth

Only one study reported this outcome but found no statistically significant difference in length gain (cm/week) between the probiotic and control groups (p=0.124) [median (range) of 1.4 (0 to 3) for the probiotic group (n=41) compared to 1.5 (0 to 3.5) for the control group (n=34)] [40].

Head growth

Only one study reported this outcome but found no statistically significant difference in head growth (cm/week) between the probiotic and control groups (p=0.124) [median (range) of 1.1 (0.45 to 1.9) for the probiotic group (n=41) compared to 0.9 (0 to 2) for the control group (n=34)] [40].

Secondary outcomes

Complications

Necrotizing enterocolitis [NEC]

Two studies (n=162) reported on NEC and their results were pooled in a meta-analysis [39, 40]. Administration of probiotics failed to significantly reduce the risk of NEC compared to controls (RR 0.42, 95% CI: 0.15 to 1.16). No significant heterogeneity was observed (Chi²=1.06, p=0.30, I²=6%) (Figure 5).

Figure 5

Effect of probiotic administration on NEC.

Sepsis

Two studies (n=162) reported on sepsis and their results were pooled in a meta-analysis [39, 40]. Administration of probiotics failed to significantly reduce the risk of sepsis compared to controls (RR 0.40, 95% CI: 0.11 to 1.45. No significant heterogeneity was observed (Chi²=1.18, p=0.28, I²=15%). (Figure 6)

Figure 6

Effect of probiotic administration on sepsis.

Other infections

No study reported on this outcome.

Mortality

Only one study [42] reported on mortality. The risk ratio for this one study (n=30) was calculated and it showed that the probiotics failed to significantly reduce the risk of death compared to the control (RR 0.33, 95% CI: 0.04 to 2.85).

Number of days on parenteral nutrition

No study reported on this outcome.

Number of days to full enteral feed

Two studies reported this outcome but their results could not be pooled in a meta-analysis because they reported the outcome in terms of medians and ranges [39, 40]. Costalos 2003 reported no statistically significant difference in the number of days to full enteral feeding between the two groups (p>0.1) [median (IQR) of 9.3 (2.7) for the probiotic group (n=51) and 9.9 (4.5) for the control group (n=36)] [32]. Stratiki 2007 also reported no statistically significant difference in the number of days to full enteral feeding [median (range) of 10 (0 to 52) for the probiotic group (n=41) and 10 (0 to 30) for the control group (n=34)] [40].

Maximal enteral feed

All four studies reported on this outcome [39–42]. Results from two studies (n=34) were pooled in a meta-analysis as they both reported the average amount of feeding (ml/day) in terms of mean (SD) [41, 42]. There was no statistically significant difference in the mean amount of feeding (ml/day) between the probiotic and control groups (MD 35.20, 95% CI: -7.61 to 78.02) No statistically significant heterogeneity was observed between the studies (Chi²=1.65, p=0.20, I²=39%).

Costalos 2003 reported no statistically significant difference in the milk intake (ml/kg/day) at maximal enteral feeding (p>0.1) [median (IQR) of 155 (15) for the probiotic group (n=51) versus 148 (13) for the control group (n=36)] [39]. Stratiki 2007 also reported no statistically significant difference in the maximal milk intake (ml/kg/day) (p=0.624) [median (range) of 210 (165 to 250) for the probiotic (n=41) group versus 192 (120 to 250) for the control group (n=34)] [40].

Feed tolerance: vomiting, gastric aspirate, abdominal distension

Two studies (n=107) reported on vomiting and were pooled in a meta-analysis [39, 42]. There was no statistically significant difference in the frequency of vomiting between the probiotic and control groups (RR 0.78, 95% CI: 0.18 to 3.37). No statistically significant heterogeneity was observed (Chi²=0.41, p=0.52, I²=0%).

In all four probiotic studies, there were no reported incidences of gastric aspirates, abdominal distension or diarrhea. Authors were further contacted for clarification and one responded [42] and stated categorically that none of these symptoms were observed.

Stool characteristics

Stool frequency

Only one study (n=20) reported stool frequency as the number of episodes of evacuations per day in terms of mean (SD) [42]. The mean difference for this one study was calculated and it showed that probiotic consumption resulted in a statistically significant larger number of stools per day compared to the control group (MD 1.60, 95% CI: 1.20 to 2.00).

Stool consistency

No study reported on the effects of probiotics on stool consistency.

Changes in intestinal permeability

Two studies reported this outcome but their results could not be pooled in a meta-analysis [39, 40]. The studies used two different tests to test for intestinal permeability. Costalos 2003 used a 1-hour D-Xylose blood test and reported no statistically significant difference between the two groups (p>0.1) [median (IQR) of 1.5 (0.4) millimols/L for the probiotics (n=51) and 1.35 (0.3) mmol/L for the control (n=36)] [39]. Stratiki 2007 used a lactulose/mannitol (L/M) urine test and reported no statistically significant difference in the L/M ratios between the probiotic and control groups (p=0.073) but the values for median (range) were presented in a figure from which they could not be accurately extracted [40].

Changes in gastrointestinal micro flora

Bifidobacteria

Two studies reported on bifidobacteria but their results could not be pooled in a meta-analysis [39, 40]. Costalos 2003 reported a significantly higher log viable Bifidobacteria counts per gram of positive infants in the probiotics group compared to the controls (p<0.001) [median (IQR) of 2.65 (0.083) for the probiotics group (n=51) and 2.27 (0.075) for the control group (n=36)] [39]. Stratiki 2007 reported bifidobacteria in terms of log 10 cfu/g wet feces but found no statistically significant difference between the two groups (p=0.075) [median (range) of 9.7 (7.5-10.3) for the probiotics group (n=41) and 8.9 (7.2-10.2) for the control group (n=34)] [40].

Lactobacillus

Only one study reported on lactobacillus [39]. This study reported no statistically significant difference in the log viable bacterial lactobacillus counts per gram of positive infants between the two groups (p>0.05) [median (IQR) of 1.57 (0.285) for the probiotics group (n=51) and 1.42 (0.287) for the control group (n=36)].

Pathogens

Only one study reported this outcome (enterococci, bacteroides, and staphylococci) in terms of the median (IQR) of log viable bacterial counts per gram of positive infants [39] (Table 6). The study reported significantly higher counts of Enterococci (p<0.05) and Staphylococci (p<0.001) in the probiotic group compared to the controls. However, the study found no statistically significant difference in the counts of bacteroides between the two groups (p>0.05).

Table 6 Log viable bacteria counts per gram of stool in positive infants fed probiotics

Prebiotic versus control

Four studies investigated the effect of prebiotics administration versus no prebiotics (control group) [36, 43–45].

Primary outcomes: short-term growth parameters

Weight gain

All four studies reported on weight gain [36, 43–45]. Results from three studies (n=106) were pooled in a meta-analysis [36, 43, 45]. Moderate heterogeneity was observed between the studies (Chi²=4.04, p=0.13, I²=51%). An investigation of heterogeneity by subgroup analysis with respect to the prebiotic type used (GOS/ FOS versus FOS only) yielded statistically significant subgroup differences (Chi²=4.04, df=1, p=0.04, I²=75.2%) implying that prebiotic type may be the source of heterogeneity. There was no statistically significant heterogeneity between the two studies in the GOS/ FOS subgroup (Chi²=0.01, df=1, p=0.94, I²=0%) [36, 43]. The results for the GOS/FOS subgroup yielded no significant difference in weight gain (g/ day) between the two groups (MD 0.04, 95% CI: -2.65 to 2.73, n=50, 2 studies) while the other FOS subgroup yielded a significantly higher weight gain in controls compared to the prebiotics (MD −4.60, 95% CI: -8.24 to −0.96, n=56, 1 study). (Figure 7) Sensitivity analysis with respect to study quality could not be done because all three studies were of poor quality since the methods used for sequence generation, allocation concealment and blinding were all not clear.

Figure 7

Effect of prebiotic administration of weight gain (g/day).

Mihatsch 2006 reported no statistically significant difference in weight gain (g/kg/day) between the two groups (p=0.4) [median (range) of 17.6 (8.1 to 23.4) for the prebiotic group (n=10) compared to 13 (9.3 to 21.9) for the control group (n=10)] [44].

Linear growth

Three studies reported on length gain [36, 43, 45]. Meta-analysis of the results from these three studies (n=106) revealed significant heterogeneity between the three studies (Chi² = 139.41, df = 2, p < 0.00001, I² = 99%). An investigation of heterogeneity by subgroup analysis with respect to the prebiotic type used (GOS/ FOS versus FOS only) yielded statistically significant subgroup differences (Chi²=139.41, df=1, p<0.00001, I²=0%) implying that prebiotic type may be the source of heterogeneity. There was no statistically significant heterogeneity between the two studies in the GOS/ FOS subgroup (Chi²=0.17, df=1, p=0.68, I²=0%). [36, 43]. The results for the GOS/FOS subgroup yielded no statistically significant difference in length gain (cm/ week) between the two groups (MD 0.01, 95% CI: -0.03 to 0.04, n=50, 2 studies) while the other FOS subgroup yielded a significantly higher length gain (cm/ week) in prebiotics compared to the controls (MD 0.30, 95% CI: 0.27 to 0.33, n=56, 1 study). (Figure 8) Sensitivity analysis with respect to study quality could not be done because all three studies were of poor quality since the methods used for sequence generation, allocation concealment and blinding were all not clear.

Figure 8

Effect of prebiotic administration of linear growth (cm/week).

Head growth

Two studies reported on head growth (cm/week) [43, 45]. Meta-analysis of the results from these two studies (n=76) failed to yield statistically significant difference in head growth (MD −0.01, 95% CI: -0.02 to 0.00). No significant heterogeneity was detected between the two studies (Chi² = 0.10, p =0.75, I² = 0%).

Secondary outcomes

Complications

No prebiotic study reported on Necrotizing Enterocolitis (NEC), Sepsis, other infections and mortality.

Feeding tolerance

Number of days on parenteral nutrition

No study reported on parenteral nutrition.

Age at full enteral feed

Two studies reported on age at full enteral feeds [36, 45]. Meta-analysis of the results from these two studies (n=86) did not find statistically significant difference in the age at full enteral feed (MD −0.79, 95% CI: -2.20 to 0.61). No significant heterogeneity was detected between the two studies (Chi² =1.16, p =0.28, I² = 14%).

Maximal enteral feed

Two studies reported on this outcome but their results could not be pooled in a meta-analysis [36, 44]. Boehm 2002 reported the feeding volume (ml/kg/day) in terms of the mean (SD) and therefore a mean difference was calculated. There was no statistically significant difference in feeding volume between the prebiotics group (n=15) and control groups (n=15) (MD −4.10, 95% CI: -18.16 to 9.96) [36].

Mihatsch 2006 reported no statistically significant difference in the average formula intake within the study period (ml/kg/d) between the two groups (p=0.35) [median (range) of 156 (127 to 165) for the prebiotic group (n=10) compared to 151 (117 to 169) for the control group (n=10)] [44].

Feed tolerance: vomiting, gastric aspirate, abdominal distension, diarrhea

All four studies reported this outcome [36, 43–45]. In all 4 studies (n=126), there were no observed incidences of feed intolerance. There was no vomiting, gastric aspirate removed, no abdominal distension or diarrhea reported. All infants tolerated the preterm formula with prebiotic or control. From further communication with study authors, 2 study authors [43, 44] responded that none of these outcomes were observed.

Stool characteristics

Stool frequency

Three studies reported on stool frequency [36, 44, 45]. Two studies reported the results in form of mean (SD) of the number of stools per day (number/ day) [36, 45]. Meta-analysis of results from these two studies (n=86) showed a significantly higher stool frequency in the prebiotic group compared to the control group (MD 0.80, 95% CI: 0.48 to 1.1). No significant heterogeneity was detected between the two studies (Chi² =0.13, p =0.72, I² = 0%) (Figure 9).

Figure 9

Effect of prebiotic administration on stool frequency.

Mihatsch 2006 reported no statistically significant difference in stool frequency between the two groups (p=0.059) [median (range) of 3.6(1.7 to 6.9) stools/day in prebiotic group (n=10) compared to 2.6 (2 to 4.9) stools/day in control group (n=10)] [44].

Stool consistency

Three studies reported on stool consistency but using three different scales of measurement [36, 44, 45]. Although two studies [36, 45] both measured consistency in form of a scale ranging from 1 to 5 and reported their results as mean (SD), they could not be pooled in a meta-analysis because their scales were going in opposite directions; Boehm 2002 (1=watery, 2=soft, 3=seedy, 4=formed, 5=hard) [36]. Kapiki 2007 (5=watery, 4=loose, 3=soft, 2=firm, hard=1) [45]. The mean differences for these two studies were therefore calculated separately.

In Boehm 2002, the stools from the prebiotic group (n=15) were significantly more watery as compared to the control group (n=15). (MD −0.91, 95% CI: -1.41 to −0.37) [36]. In Kapiki 2007, the stools from the prebiotic group (n=36) were significantly harder as compared to the control group (n=20). (MD −0.34, 95% CI: -0.66 to −0.02) [45].

Mihatsch 2006 reported a statistically significantly lower stool viscosity at day 14 (Newtons) for the prebiotics compared to controls (p=0.006) [median (range) of 31.8 (1.9 to 67.3) in the prebiotic group (n=10) compared to 157.5 (24.1 to 314.0) in the control group (n=10)] [44].

Changes in intestinal permeability

No prebiotic study reported on changes in intestinal permeability.

Changes in gastrointestinal micro flora

Bifidobacteria

Two studies reported on this outcome [36, 45]. Meta-analysis of these two studies (n=84) revealed statistically significant heterogeneity between the two studies (Chi² =7.63, p =0.006, I² = 87%). An investigation of heterogeneity by subgroup analysis with respect to the prebiotic type used (GOS/ FOS versus FOS only) yielded statistically significant subgroup differences (Chi² =7.63, p =0.006, I² = 86.7%) implying that prebiotic type may be the source of heterogeneity. The results for the GOS/FOS subgroup yielded significantly higher bifidobacteria counts in prebiotics compared to controls (MD 2.10, 95% CI: 0.96 to 3.24) [36]. The other FOS subgroup also yielded significantly higher bifidobacteria counts in prebiotics compared to controls (MD 0.48, 95% CI: 0.28 to 0.68) [45] (Figure 10).

Figure 10

Effect of prebiotic administration on total counts of Bifidobacteria.

Lactobacilli

Only one study [36] reported this outcome but the actual values were not given.

Pathogens [Post-intervention]

Two studies reported on this but their results could not be pooled in a meta-analysis [36, 45]. Boehm 2002 reported the sum of clinically relevant pathogens at the end of the intervention period in the form of mean (SD) log cfu/g stool. The values were used to calculate the mean difference which showed that the sum of the studied pathogens was significantly lower in the prebiotic group (n=12) compared to the control group (n=13). (MD −0.43, 95% CI: -0.79 to −0.07) [36].

Kapiki 2007 reported this outcome (staphylococci, E. coli, bacteroides, and enterococci) in terms of mean (SD) log 10 CFU/g wet feces [45]. Mean differences for each of these pathogens were calculated. There was no statistically significant difference in the number of staphylococci (MD 0.00, 95% CI: -0.17 to 0.17) between the two groups but there were significantly fewer E. coli (MD −1.69, 95% CI: -1.85 to −1.53) and enterococci (MD −0.80, 95% CI: -0.99 to −0.61) in the prebiotic group (n=36) compared to the control group (n=20). With regards to bacteroides, there were significantly more bacteroides in the prebiotic group (n=36) compared to the control group (n=20) (MD 0.50, 95% CI: 0.36 to 0.64) [45].

Discussion

The objective of this review was to assess if addition of probiotics or prebiotics to preterm infant formula led to improved growth and clinical outcomes in preterm or low birth weight infants. Studies that used breast milk or mixed feeds (breast milk and infant formula) were excluded. All RCTs evaluated probiotics or prebiotic use in preterm infants, were of small sample size, varied in enrolment criteria, intervention, treatment initiation and duration.

Summary of main findings

Probiotics

This review was under powered to detect clinically important differences in primary outcomes (weight gain, linear growth, head growth) because of the few number of studies, small sample size (n=34) and poor methodological quality of studies. This review found no significant effect on weight gain from use of probiotics added to infant formula. There was also no significant probiotic effect on linear and head growth from the one study measuring these two outcomes. Probiotic supplementation failed to significantly reduce the risk of complications such as NEC, sepsis and death compared to control group. Outcomes such as number of days on parenteral nutrition and other infections were not reported. There was no significant difference in the amount of feed volume (ml/day) and frequency of vomiting between study groups. Preterm infant formula with probiotics was well tolerated as no gastric aspirates, abdominal distension or diarrhea was reported. Effects of probiotics on stool characteristics were under reported. Results from one study showed probiotics supplementation did result in a larger number of stools per day.

Effects on intestinal permeability could not be evaluated since two different laboratory tests (lactulose / mannitol ratio and D- xylose tests) were reported and the results could not be pooled. Sugar absorption tests (such as lactulose / mannitol ratio) are a direct measure of intestine integrity which reflects gut maturation and in research; they demonstrate the effects of experimental therapy [78, 79]. Monitoring changes in intestinal permeability in preterm infants is essential since there is evidence that initiation of enteral feeds decreases intestinal permeability [78, 80]. However, this could not be established in this review. Other outcomes such as age at full enteral feeds and intestinal micro flora (pathogens) could not be evaluated as medians (inter quartile ranges) were reported. No probiotic study reported any data on low birth weight infants therefore no conclusions could be made on this population.

The included probiotic studies had short treatment duration of 30 days. This confirms the European Society for Pediatric, Gastroenterology, Hepatology and Nutrition (ESPGHAN) statement that there is a “lack of published evidence on clinical benefits from long term use of probiotic containing infant formula” [81]. This review confirms that there is a need for long term follow-up RCTs on preterm infants. Live probiotic bacteria were used in the trials. There have been few reports of bacteraemia from probiotic use in the biomedical literature [82–84]. There were no cases of sepsis reported as a result of probiotic consumption in the included studies. In recent reviews, the time to reach full enteral feeds was earlier in the preterm infants given probiotics with breast milk or mixed feeds. This review could not evaluate this outcome. Well-designed RCTs with similar feeding regimes are needed to evaluate this outcome.

Prebiotics

This review was under powered to detect clinically important differences in primary outcomes (weight gain, linear growth, head growth) because of few number of studies, small sample size (n=106) and poor methodological quality of studies. Addition of prebiotic combinations of GOS /FOS or FOS alone to preterm infant formula did not have any significant effect on weight gain. Addition of GOS / FOS to preterm infant formula did not have any effect on linear growth. However, addition of FOS alone did have a significant effect on linear growth. Neither GOS / FOS combination nor FOS alone had any effect on head growth.

None of the prebiotic studies reported on NEC, sepsis, other infections, mortality (death), parenteral nutrition or changes in intestinal permeability; therefore these outcomes could not be evaluated. Prebiotics did not have any significant effect on the age at which infants reached full enteral feeds or volume of feed tolerated. Prebiotic preterm formula was well tolerated because there were no reports of vomiting, gastric aspirates, abdominal distension or diarrhea. Prebiotic supplementation did result in a higher stooling frequency compared to control. Effects on stool consistency were inconclusive as results from one study resulted in more watery stools in the prebiotic study group compared to control group, in a second study, the prebiotic group experienced harder stools compared to control group. The third study results were presented in medians (range) therefore no conclusions could be made. In preterm infants, frequent watery stools may signify intolerance, a transient lactase deficiency or another pathological state which always require further investigation [6].

Prebiotics did have a significant effect on intestinal micro flora. Addition of GOS / FOS combination or FOS alone significantly increased counts of bifidobacteria. Effects on lactobacillus counts could not be evaluated as actual figures were not available. The sum of studied pathogens and some selected pathogens (E- coli, enterococci) were significantly fewer in the prebiotic group compared to control group. There was no effect on staphylococci levels while bacteroides were significantly higher in the probiotic group compared to control group. No prebiotic study reported any data on low birth weight infants; therefore no evaluations could be made.

The prebiotic studies were of short duration ranging from 14 to 28 days. The dose of the prebiotic used (GOS, FOS) varied from 0.4 g/dl o 1g/dl. The European Committee on Food recommends that prebiotics added to formula milk do not exceed 0.8 g/100 ml. The rationale for prebiotic doses not exceeding 1g/ml in clinical trials is an attempt to maximize the bifidogenic effect with minimal intolerance as exhibited by, abdominal distension [85]. The preterm infants tolerated the prebiotic formula as there were no symptoms of feed intolerance reported.

Prebiotic supplementation did have some short term benefits: increased stooling frequency and bifidobacteria counts, fewer pathogens in the prebiotic group compared to control group. However, large RCTS with long term follow -up are needed to find out if these short term benefits translate into improved general health and reduced morbidities in preterm infants. Due to the short duration of prebiotic studies, routine supplementation with prebiotics in preterm infants cannot be recommended.

Quality of the evidence and potential biases

In this review, the quality of the evidence was compromised by several factors: Sample size: included studies were of small individual sample size, number of study participants ranged from 20 to 87 in the probiotic studies, 20 to 56 in prebiotic studies. Intervention: Different types of probiotic and prebiotics, doses and treatment duration were used. Methodological quality: Inadequate information was published to assess methodological quality of the studies. Information was missing on sequence generation, allocation concealment, blinding, incomplete outcome data, selective reporting and free of other bias domains. The significance of any relationship between methodological quality and study outcomes could not be verified since no subgroup analysis with respect to study quality could be done as a result of either too few studies in a meta-analysis or having all studies with similar quality in a meta-analysis. Not all the reviews pre- specified outcomes were addressed by the included studies.

At the conclusion of the review process and preparation of the manuscript (for this review), one on- going study was terminated due to being under powered [47]. One study was completed and data analysis commenced. The results from this study could not be included in this review [48]. The other three studies were still on-going [46, 49, 50]. The reviewers used thorough comprehensive search strategies adopted for the available databases. All attempts were made to minimize publication bias. All steps of this review were conducted independently by the reviewers.

Agreements and disagreements with other reviews

No significant difference was found in contrast with past reviews and that the potential reasons are lack of power, poor quality of studies or a lack of effect in formula fed infants. This review did agree with some aspects of past reviews. Prebiotics did have an impact on GI micro flora (increased bifidobacteria counts, reduction in certain pathogens); feed tolerance (no reported gastric aspirates, abdominal distension).

Conclusion

There is not enough evidence to state that supplementation of preterm infant formula with probiotics or prebiotics does result in improved growth and clinical outcomes in preterm infants. Therefore this review does not support the routine supplementation of preterm formula with probiotics or prebiotics.

Implications for research

For clear recommendations to be made, long term large RCTs on exclusively formula fed preterm and low birth weight infants are required to investigate the effects of probiotics and prebiotics supplementation in preventing NEC, sepsis, death/mortality; changes in intestinal micro flora and intestinal permeability; explore the efficacy of different doses of the same probiotic on clinical outcomes because available studies used different probiotic doses; similarly, explore the efficacy of different doses of the same prebiotic on clinical outcomes because available studies used similar prebiotics with different doses and treatment duration.