Biocare Hepaguard Forte Vegetable - Pack of 60 Capsules

£9.9
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Biocare Hepaguard Forte Vegetable - Pack of 60 Capsules

Biocare Hepaguard Forte Vegetable - Pack of 60 Capsules

RRP: £99
Price: £9.9
£9.9 FREE Shipping

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Description

They found 202 randomised clinical trials (studies where participants are randomly assigned to one of two treatment groups). Well‐designed trials that collect data over longer follow‐up times are needed in the future to find out the best nutritional supplementation (if any) for people with NAFLD.

Low risk of bias: the trial reported the following pre‐defined outcomes: at least one of the outcomes related to the main reason for treatment of people with NAFLD, namely, all‐cause mortality or resolution of NAFLD, along with adverse events. We included randomised clinical trials with participants who have non‐alcohol‐related fatty liver disease (NAFLD), irrespective of method of diagnosis, age and diabetic status of participants, or presence of non‐alcoholic steatohepatitis (NASH).We estimated the probability that each intervention was ranked at each of the possible positions based on estimated effect sizes and their corresponding uncertainty using the NICE DSU codes ( Dias 2016). If it was not possible to calculate the standard deviation from the P value or from the confidence intervals, we planned to impute the standard deviation using the largest standard deviation in other trials for that outcome. The thickness of the line provides a measure of the number of direct comparisons between two nodes (interventions). For all direct comparisons and for network meta‐analysis involving clinical outcomes, events were fewer than 300, and we downgraded one level for imprecision.

We used a normal distribution with large variance (10,000) for treatment effect priors (vague or flat priors) centred at no effect. For outcomes for which we were able to assess heterogeneity, there was evidence of heterogeneity for any adverse events (number of events); therefore, we downgraded one more level for heterogeneity for this outcome. The remaining 182 trials were at unclear or high risk of bias in at least one domain and were considered to be at high risk of bias overall. In all, 48 trials were at low risk of selective outcome reporting bias, as the important clinical outcomes expected to be reported in such trials were reported; the remaining 154 trials were at high risk of selective outcome reporting bias as outcomes were changed from the protocol published prior to recruitment without sufficient justification, or trials did not report reasonably expected clinical outcomes if no protocol was published prior to recruitment. We considered variations in subcategories, for example, different doses or durations of nutritional supplementation, as the same treatment node.

We also performed a sensitivity analysis that excluded trials in which mean or standard deviation, or both, were imputed, and we used the median standard deviation in trials to impute missing standard deviations. We performed a network meta‐analysis with OpenBUGS using Bayesian methods whenever possible and calculated differences in treatments using hazard ratios (HRs), odds ratios (ORs), and rate ratios with 95% credible intervals (CrIs) based on an available‐case analysis, according to National Institute of Health and Care Excellence Decision Support Unit guidance. We assessed inconsistency (statistical evidence of violation of the transitivity assumption) by fitting both an inconsistency model and a consistency model.



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