{smcl}
{* *! version 1.00 15daugust2007}{...}
{hline}
help for {hi:midas9} {right: (Ben Adarkwa Dwamena)}
{hline}
{title:midas9 -- Meta-analytical Integration of Diagnostic Accuracy Studies}
{title:Syntax}
{p 8 18 2}
{opt midas9}
{it:varlist}
[{opt if} {it:exp}]
[{opt in} {it:range}]
[{opt ,}
{opt id(varname)}
{opt year(varname)}
{it:modeling_options}
{it:quality_assessment_options}
{it:reporting_options}
{it:exploratory_graphics_options}
{it:publication_bias_Options}
{it:forest_plot_options}
{it:heterogeneity_options}
{it:roc_options}
{it:probability_revision_options}
{it:general_graphing_options} *]
{p 12 12 2}
{it:modeling_options} may be
{opt nip(integer 15)}
{opt es:timator()}
{p 12 12 2}
{it:quality_assessment_options} may be
{opt qualit:ab}
{opt qualib:ar}
{opt qlab}
{p 12 12 2}
{it:reporting_options} may be
{opt res:ults()}
{opt tab:le()}
{p 12 12 2}
{it:exploratory_graphics_options} may be
{opt chip:lot}
{opt biv:box}
{opt qq:plot}
{opt cum}
{opt inf}
{p 12 12 2}
{it:publication_bias_options} may be
{opt pubb:ias}
{opt fun:nel}
{opt maxbias}
{p 12 12 2}
{it:forest_plot_options} may be
{opt for:est()}
{opt ford:ata}
{p 12 12 2}
{it:heterogeneity_options} may be
{opt galb()}
{opt het:for}
{opt cov:ars}
{p 12 12 2}
{it:roc_curve_options} may be
{opt sroc1}
{opt sroc2}
{opt rocp:lane}
{p 12 12 2}
{it:probability_revision_options} may be
{opt pddam()}
{opt fagan}
{opt prior()}
{opt lrm:atrix}
{p 12 12 2}
and {it:general_graphing_options} may be
{opt plot:type(string)}
{opt test:lab(string)}
{opt csize(real 36)}
{opt hsize(integer 6)}
{opt vsize(integer 8)}
{opt level(integer 95)}
{opt ms:cale(real 0.50)}
{opt texts:cale(real 0.85)}
{opt zcf(real 0.5)}
{p 4 4 2}
{opt by}{it:...}{cmd ::} may be used with {help midas9}; see help {help by}.
{title:Description}
{pmore}
{help midas9} is a comprehensive program of statistical and graphical routines
for undertaking meta-analysis of diagnostic test performance in Stata.
{pmore}
Primary data synthesis is performed within the bivariate mixed-efects binary
regression modeling framework. Model specification, estimation and prediction
are carried out with {help gllamm}(Rabe-Hesketh et.al) in release 9, by adaptive quadrature.
{pmore}
Using the model estimated coefficients and variance-covariance matrices,
{help midas9} calculates summary operating sensitivity and specificity
(with confidence and prediction contours in SROC space), summary likelihood
and odds ratios. Global and relevant test performance metric-specific
heterogeneity statistics are provided.
{help midas9} facilitates extensive statistical and graphical data
synthesis and exploratory analyses of heterogeneity, covariate effects,
publication bias and influence.
{pmore}
Bayes' nomograms and likelihood ratio matrices may be obtained and used to
guide clinical decision-making.
{pmore}
The minimum required varlist is the data from contingency tables of test results.
The user provides the data in a rectangular array containing variables for
the 2x2 elements a, b, c, and d:
{p_end}
2x2 +{hline 21}+
table | Test |
+{hline 9}+{hline 10}+{hline 10}+ where:
| Truth | Positive | Negative | a = true positives,
+{hline 9}+{hline 10}+{hline 10}+ b = false positives,
| Case | a | c | c = false negatives,
+{hline 9}+{hline 10}+{hline 10}+ d = true negatives.
| Noncase | b | d |
+{hline 9}+{hline 10}+{hline 10}+
{pmore}
Each data file row contains the 2x2 data for one observation (i.e., study).
{pmore}
{opt id(varname)} {opt year(varname)}, if provided , is concatenated to create
a study identification variable. Default uses observation number for id.
{pmore}
The varlist MUST contain variables for a, b, c, and d in that order.
{pmore}
Note: {help midas9} requires release 10 to implement modeling with {help xtmelogit}
or Stata version 9 for estimation with {help gllamm} (mainly because of
use of paired coordinate arrow graphics not available before release 9);
{pmore}
User should install (if not installed) {help metan} and {help mylabels}
for either estimator and also {help gllamm} if using release 9.
{dlgtab:Modeling}
{pmore}
{opt nip} specifies the number of integration points used for maximum likelihood
estimation based on adaptive gaussian quadrature. Default is set at 15 for
{opt midas9} even though the default in {help xtmelogit} is 7.
Higher values improve accuracy at the expense of execution times.
The only values currently supported by {help gllamm} are 5, 7, 9, 11 and 15
(Rabe-Hesketh & Skrondal 2005}, appendix B.)
{pmore}
Using {help xtmelogit} with {opt nip(1)}, model will be estimated by
Laplacian approximation. This decreases substantially computational
time and yet provides reasonably valid fixed effects estimates.
It may, however, produce biased estimates of the variance components.
{pmore}
{opt es:timator(g|x)} provides a choice between estimation with
{help xtmelogit} in release 10 versus {help gllamm} in version 9 or earlier.
{pmore}
The following options MUST have an estimator inorder to work!
{opt pddam()}, {opt fagan}, {opt for:est()},{opt rocp:lane}, {opt sroc1},
{opt sroc2}, {opt het:for}, {opt res:ults()}, {opt tab:le()} and {opt lrm:atrix}.
if estimator is missing, {help midas9} will issue an error message.
{dlgtab:Quality_Assessment}
{pmore}
{opt qualit:ab} creates, using optional varlist of study quality items
(presence=1, other=0) a table showing frequency of methodologic quality items.
{pmore}
{opt qualib:ar} creates, combined with optional varlist of study
quality items (presence=1, other=0) calculates study-specific quality scores
and plots a bargraph of methodologic quality.
{pmore}
{opt qlab} may be combined with {opt qualitab} or {opt qualibar} to use
variable labels for table and bargraph of methodologic items.
{dlgtab:Reporting}
{pmore}
{opt res:ults(all)} provides summary statistics for all performance
indices, group-specific between-study variances, likelihood rato
test statistics and other global homogeneity tests.
{pmore}
{opt res:ults(het)} provides group-specific between-study variances,
likelihood rato test statistics and other global homogeneity tests.
{pmore}
{opt res:ults(sum)} provides summary statistics for all performance indices
{pmore}
{opt tab:le(dss|dlr|dlor)} will create a table of study specific
performance estimates with measure-specific summary estimates and results
of homogeneity (chi_squared) and inconsistency(I_squared) tests.
{opt dss}, {opt dlr} or {opt dlor} represent the paired performance
measures sensitivity/specificity, positive/negative likelihood ratios
and diagnostic score/odds ratios.
{dlgtab:Exploratory Graphics}
{pmore}
{opt bivbox} implements a two-dimensional analogue of the boxplot for
univariate data similar to the bivariate boxplot
(Goldberg and Iglewicz,1992). It is used to assess distributional
properties of sensitivity versus specificity and for indentifying
possible outliers.
{pmore}
{opt chi:plot} creates a chiplot (Fisher & Switzer, 1985, 2001) for
judging whether or nor the paired performance indices are independent
by augmenting the scatterplot with an auxiliary display. In the case
of independence, the points will be concentrated in the central region,
in the horizontal band indicated on the plot.
{pmore}
{opt qq:plot(dss|dlor|dlr)} plots a normal quantile plot to
(a) check the normality assumption
(b) investigate whether all studies come from a single population
(c) search for publication bias (Wang and Bushman, 1998).
{pmore}
{opt cum} produces a cumulative meta-analysis plot showing how evidence
has accumulated over time using {help metan} (most current version must
be installed and may be obtained my typing {ssc install metan, replace}).
{help midas9} uses year of publication as measure for temporal
evolution of evidence.
{pmore}
Results are displayed graphically using {opt serrbar}.
The ith line on the plot is the summary produced
by a meta-analysis of the first ith trials.
{pmore}
{opt inf} investigates the influence of each individual study on the
overall meta-analysis summary estimate. This option presents a {help serrbar}
of the results of an influence analysis in which the meta-analysis is reestimated
omitting each study in turn, using {help metan} (most current version
must be installed).
{dlgtab:Publication Bias}
{pmore}
{opt pubb:ias} When this option is invoked, midas9 performs linear regression
of log odds ratios on inverse root of effective sample sizes as a test
for funnel plot asymmetry in diagnostic metanalyses. A non-zero slope coefficient
is suggestive of significant small study bias(pvalue < 0.10).
{pmore}
{opt max:bias} performs Copas' worst-case sensitivity analysis for
publication bias. It calculates the upper bound number of missing studies
that will overturn statistical significance and estimates the minimun likely
publication probability (Copas and Jackson, 2004).
{pmore}
{opt fun:nel} plots a funnel plot, a two-dimensional graph with sample size on
one axis and effect-size estimate on the other axis. The funnel plot
capitalizes on the well-known statistical principle that sampling error decreases
as sample size increases.
{pmore}
In a meta-analysis, the funnel plot can be used to investigate whether all
studies come from a single population and to search for publication bias.
{dlgtab:Forest Plots}
{pmore}
{opt for:est(dss|dlr|dlor)} creates summary graphs with study-specific(box) and
overall(diamond) point estimates and confidence intervals for each performance
index pair using graph combine. Confidence intervals lines are allowed to extend
between 0 and 1000 beyond which they are truncated and marked by a leading arrow.
{pmore}
{opt ford:ata} adds study-specific performance estimates and 95% CIs to right y-axis.
{dlgtab:Heterogeneity}
{pmore}
{opt galb(dss|dlr|dlor)} The standardized effect measure (e.g. for lnDOR, lnDOR/precision) is plotted (y-axis) against
the inverse of the precision(x-axis). A regression line that goes through the
origin is calculated, together with 95% boundaries (starting at +2 and -2 on the y-axis).
Studies outside these 95% boundaries may be considered as outliers.
{pmore}
{opt het:for} creates composite forest plot of all performance indices to
provide a general view of variability.Confidence intervals lines are allowed
to extend between 0 and 1000 beyond which they are truncated and marked by a
leading arrow.
{pmore}
{opt cov:ars} combined with an optional varlist permits univariable metaregression
analysis of one or multiple covariables.
{dlgtab:ROC Curves}
{pmore}
{opt sroc1} plots observed datapoints, summary operating sensitivity and
specificity in SROC space.
{pmore}
{opt sroc2} adds confidence and prediction contours.
{pmore}
{opt roc:plane} plots observed data in receiver operating characteristic
space (ROC Plane) for visual assessment of threshold effect.
{dlgtab: Probability Revision Options}
{pmore}
{opt fagan} creates a plot showing the relationship between the prior probability,
the likelihood ratio(combination of sensitivity and specificity), and posterior
test probability.
{pmore}
{opt prior()} combined with {opt fagan} allows user to specify a pretest
probability overriding the default of using disease prevalence calculated
from data when {opt fagan} is invoked alone.
{pmore}
{opt pddam(p|r)} produces a line graph of post-test probalities versus
prior probabilities between 0 and 1 using summary likelihood ratios
{pmore}
{opt lrm:atrix} creates a scatter plot of positive and negative likelihood
ratios with combined summary point. Plot is divided into quadrants based on
strength-of-evidence thresholds to determine informativeness of measured test.
{dlgtab:Graphing Options}
{pmore}
{opt plot:type(string)} will add type of plot to title of plot
{pmore}
{opt test:lab(string)} will add any descriptive string to title of plot
{pmore}
{opt csize()} allows user to modify relative sizes of combined forest
plots along the x axis.
{pmore}
{opt hsize()} allows user to modify size of other plots along the x axis.
{pmore}
{opt vsize()} allows user to modify relative sizes of combined forest
plots along the y axis.
{pmore}
{opt level()} specifies the significance level for statistical tests, confidence
contours, prediction contours and confidnce intervals.
{pmore}
{opt mscale()} affects size of markers for point estimates on forest plots.
{pmore}
{opt scheme(string)} permits choice of scheme for graphs. The default is s2color.
{pmore}
{opt texts:cale()} allows choice of text size for graphs especially regarding
labels for forest plots.
{pmore}
{opt zcf()} defines a fixed continuity correction to add in the case where a
study contains a zero cell. By default, {help midas9} adds 0.5 to each cell of
a study where a zero is encountered for logit and log transformations, only to
calculate study-specific likelihood ratios and odds ratios. However, the
{opt zcf()} option allows the use of other constants between 0 and 1.
{title: Remarks on test performance metrics:}
{pmore}
Sensitivity and specificity , diagnostic odds ratio and likelihood ratios with
95% confidence intervals, are recalculated for each primary study from
the contingency tables of true-positive [a], false-positive [b], false-negative
results [c], and true-negative [d].
{pmore}
A four-fold (two by two contingency) table comparing test results for a
diagnostic/screening test is identical to a four-fold table comparing
outcomes of an experimental application of an intervention
(Skupski, Rosenberg and Eglinton, 2002).
{pmore}
For an interventional trial, the true positives are the experimental
group with the monitored outcome present [a].The false positives are the control
group with the outcome present [b]. The false negatives are the experimental group
with the outcome absent [c]. The true negatives are the control
group with the outcome absent [d]. The expression for the relative risk
in the experimental group {[a/ (a + c)]/ [b/ (b + d)]} is identical to
the expression for the likelihood ratio for a positive test in an evaluation
of a diagnostic or a screening methodology.
Similarly, the expression for the relative risk in the control group in an
interventional trial is identical to the expression for the likelihood ratio
for a negative test(Skupski, Rosenberg and Eglinton, 2002).
The LRs indicate by how much a given test would raise or lower the
probability of having disease. In order for diagnostic informativeness to be high,
an LR of > 10 or < 0.1 would be required for a positive and negative test result,
respectively. Moderate informational value can be achieved with LR values
of 5-10 and 0.1-0.2; LRs of 2-5 and 0.2-0.5 have very small informational value.
{pmore}
The diagnostic odds ratio of a test is the ratio of the odds of positivity
in disease relative to the odds of positivity in the nondiseased
(Glas, Lijmer, Prins, Bonsel and Bossuyt, 2003). The expression for the
odds ratio (DOR) is (a × d)/(b × c). The value of a DOR ranges from 0 to infinity,
with higher values indicating better discriminatory test performance.
A value of 1 means that a test does not discriminate between patients
with the disorder and those without it. Values lower than 1 point to improper
test interpretation (more negative tests among the diseased).
The diagnostic odds ratio (DOR) may be used as a single summary measure
with the caveat that the same odds ratio may be obtained with different
combinations of sensitivity and specificity (Glas, Lijmer, Prins, Bonsel and Bossuyt, 2003)
{pmore}
The area under the curve (AUROC), obtained by trapezoidal integration, serves as a global measure of test performance.
The AUROC is the average TPR over the entire range of FPR values.
The following guidelines have been suggested for interpretation of intermediate AUROC values:
low (0.5>= AUC <= 0.7), moderate (0.7 >= AUC <= 0.9), or high (0.9 >= AUC <= 1) accuracy (Swets, 1988).
{title:Remarks on Meta-analytic Model:}
{pmore}
Primarily, {help midas9} uses an exact binomial rendition (Chu & Cole, 2006) of the bivariate mixed-effects regression model
developed by von Houwelingen(von Houwelingen, 1993, 2001) for treatment trial meta-analysis and modified for synthesis of
diagnostic test data (Reitsma, 2005; Riley, 2006).
{pmore}
It fits a two-level model, with independent binomial distributions for the true positives and true negatives
conditional on the sensitivity and specificity in each study and a bivariate normal model for the {help f_logit:logit}
transforms of sensitivity and specificity between studies.
{pmore}
The standard output of the bivariate model includes: mean logit sensitivity and specificity with their standard errors
and 95% confidence intervals; and estimates of the between-study variability in logit sensitivity and specificity and
the covariance between them.
{pmore}
Based on these parameters, we can calculate other measures of interest such as the likelihood ratio for positive and
negative test results, the diagnostic odds ratio, the correlation between logit sensitivity and specificity,
several summary ROC linear regression lines based on either the regression of logit sensitivity on specificity,
the regression of logit specificity on sensitivity, or an orthogonal regression line by minimizing the perpendicular distances.
These lines can be transformed back to the originalROC scale to obtain a summary ROC curve. Summary sensitivity, specificity,
and the corresponding positive likelihood, negative likelihood and diagnostic odds ratios are drived as
functions of the estimated model parameters; The derived logit estimates of sensitivity, specificity and respective variances
are used to construct a hierarchical summary ROC curve.
{title:Remarks on assessment and exploration of heterogeneity:}
{pmore}
Heterogeneity means that there is between study variation. Galbraith(radial) plot is used to visually identify outliers.
To construct this plot, the standardized lnDOR = lnDOR/se is plotted (y-axis) against the inverse of the se (1/se) (x-axis).
A regression line that goes through the origin is calculated, together with 95% boundaries (starting at +2 and -2 on the y-axis).
Studies outside these 95% boundaries may be considered as outliers.
{pmore}
Many sources of heterogeneity can occur: characteristics of the study population, variations in the study design
(type of design, selection prodedures, sources of information, how the information is collected), different statistical methods,
and different covariates adjusted for (if relevant) (Dinnes, 2005). Heterogeneity (or absence of homogeneity) of the results
between the studies is assessed graphically by forest plots and statistically using the quantity I2 that describes the
percentage of total variation across studies that is attributable to heterogeneity rather than chance (Higgins, 2003).
{pmore}
I2 can be calculated from basic results as I2 = 100% x (Q - df)/Q, where Q is Cochran's heterogeneity statistic and
df the degrees of freedom. (Higgins, 2003). Negative values of I2 are made equal to 0 so that I2 lies between 0% and 100%.
A value of 0% indicates no observed heterogeneity, and values greater than 50% may be considered substantial heterogeneity.
The main advantage of I2 is that it does not inherently depend on the number of the studies in the meta-analysis.
{pmore}
Formal investigation of heterogeneity is performed by multiple univariable bivariate meta-regression models.
Covariates are manipulated as mean-centered continuous or as dichotomous (yes=1, no= 0) fixed effects.
The effect of each covariate on sensitivity is estimated separately from that on specificity.
Metaregression is a collection of statistical procedures (weighted/unweighted linear, logistic regression)
to assess heterogeneity, in which the effect size of study is regressed on one or several covariates, with a
value defined for each study.
{title:Remarks on Publication bias:}
{pmore}
Publication bias is produced when the published studies do not represent adequately all the studies carried out on a
specific topic (Begg and Berlin). This bias may be caused by factors such as the trend to publish
statistically significant (p < 0.05) or clinically relevant (high magnitude albeit non-significant) results.
Other variables influencing publication bias (Song, 2002) are sample size (more in small studies),
type of design, funding, conflict of interest, prejudice against an observed association, sponsorship.
{pmore}
Publication bias is assessed visually by using a scatter plot (Light and Pillemer, 1984) of the inverse of the square root of the
effective sample size (1/ESS1/2) versus the diagnostic log odds ratio(lnDOR) which should have a symmetrical funnel
shape when publication bias is absent (Deeks, 2005).
{pmore}
Separate funnel plots for sensitivity and specificity
(after logit transformation) are unlikely to be helpful for detecting sample size effects, because
sensitivities and specificities will vary due to both variability of threshold between the studies and
random variability. Simultaneous interpretation of two related funnel plots and two tests for funnel plot
asymmetry also presents challenges. Formal testing for publication bias may be conducted by a regression of
lnDOR against 1/ESS1/2, weighting by ESS (Deeks, 2005), with P < .05 for the slope coefficient indicating significant asymmetry.
{pmore}
An alternative graphical test of publication bias may be derived by assessing the linearity of the Normal
quantile plot (Wang and Bushman, 1998). This plot compares the quantiles of an observed distribution
against the quantiles of the standard Normal distribution. In a meta-analysis, such a plot can be used to
check the Normality assumption, investigate whether all studies come from a single population, and search
for publication bias (Wang and Bushman, 1998).
{title: Remarks on Cumulative meta-analysis:}
{pmore}
Cumulative meta-analysis is a type of meta-analysis in which studies are sequentially pooled by adding each time
one new study according to an ordered variable. For instance, if the ordered variable is the year of publication,
studies will be ordered by it; then, a pooling analysis will be done every time a new article appears.
It shows the evolution of the pooled estimate according to the ordered variable. Other common variables used in
cumulative meta-analysis are the study quality, the risk of the outcome in the control group, the size of the
difference between the groups, and other covariates.
{title: Remarks on Clinical Application:}
{pmore}
The clinical or patient-relevant utility of diagnostic test is evaluated using the likelihood ratios to calculate
post-test probability based on Bayes' theorem as follows (Jaeschke, 1994):
Pretest Probability=Prevalence of target condition
{pmore}
Post-test probability= likelihood ratio x pretest probability/[(1-pretest probability) x (1-likelihood ratio)]
{pmore}
Assuming that the study samples are representative of the entire population, an estimate of the pretest
probability of target condition is calculated from the global prevalence of this disorder across the studies.
{pmore}
In this way, likelihood ratios are more clinically meaningful than sensitivities or specificities.
This approach would be useful for the clinicians who might use the likelihood ratios generated from here to
calculate the post-test probabilities of nodal disease based on the prevalence rates of their own practice population.
{pmore}
Thus, this approach permits individualization of diagnostic evidence.
This concept is depicted visually with Fagan's nomograms. When Bayes theorem is expressed in terms of log-odds,
the posterior log-odds are linear functions of the prior log-odds and the log likelihood ratios.
{opt fagan} plots an axis on the left with the prior log-odds, an axis in the middle representing the log likelihood ratio
and an axis on the right representing the posterior log-odds. Lines are then drawn
from the prior probability on the left through the likelihood ratios in the center
and extended to the posterior probabilities on the right.
{pmore}
The likelihood ratio matrix defines quadrants of informativeness based on established evidence-based thresholds:
{pmore}
{hi:Left Upper Quadrant}, Likelihood Ratio Positive > 10, Likelihood Ratio Negative <0.1:
{hi:Exclusion & Confirmation}
{pmore}
{hi:Right Upper Quadrant}, Likelihood Ratio Positive >10, Likelihood Ratio Negative >0.1:
{hi:Confirmation Only}
{pmore}
{hi:Left Lower Quadrant}, Likelihood Ratio Positive <10, Likelihood Ratio Negative <0.1:
{hi:Exclusion Only}
{pmore}
{hi:Right Lower Quadrant}, Likelihood Ratio Positive <10, Likelihood Ratio Negative >0.1:
{hi:No Exclusion or Confirmation}
{title:Examples}
{p 8 12 2}
{stata "use http://repec.org/nasug2007/midas9_example_data.dta":. use http://repec.org/nasug2007/midas9_example_data.dta}
{p 4 8 2}
Summary Statistics
{p 8 12 2}
{cmd:. midas9 tp fp fn tn, es(g) res(all)}
{p_end}
{p 12 12 2}
{it:({stata "midas9_examples midas9_example_results":click to run})}
{p 4 8 2}
Table of index-specific results
{p 8 12 2}
{cmd:. midas9 tp fp fn tn, es(g) table(dlr)}
{p_end}
{p 12 12 2}
{it:({stata "midas9_examples midas9_example_table":click to run})}
{p 4 8 2}
Summary ROC Curve with prediction and confidence Contours
{p 8 12 2}
{cmd:. midas9 tp fp fn tn, es(g) plot sroc2 }
{p_end}
{p 12 12 2}
{it:({stata "midas9_examples midas9_example_srocellip":click to run})}
{p 4 8 2}
Linear regression test of funnel plot asymmetry
{p 8 12 2}
{cmd:. midas9 tp fp fn tn, pubbias}
{p_end}
{pmore2}
{it:({stata "midas9_examples midas9_example_pubbias":click to run})}
{p 4 8 2}
Funnel plot assessment of publication and other small study biases
{p 8 12 2}
{cmd:. midas9 tp fp fn tn, fun}
{p_end}
{p 12 12 2}
{it:({stata "midas9_examples midas9_example_funnel":click to run})}
{p 4 8 2}
Forest plot to demonstrate variability
{p 8 12 2}
{cmd:. midas9 tp fp fn tn,}
{p_end}
{p 12 12 2}
{cmd:id(author) year(year) ms(0.75)}
{p_end}
{phang2}
{cmd:for(dss) es(g) texts(0.80)}
{p_end}
{pmore2}
{it:({stata "midas9_examples midas9_example_forest1":click to run})}
{phang}
Forest plot to demonstrate study-specific on right y-axis
{phang2}
{cmd:.midas9 tp fp fn tn, id(author) year(year) }
{p_end}
{phang2}
{cmd:es(g) ms(0.75) ford for(dss) texts(0.80)}
{p_end}
{pmore2}
{it:({stata "midas9_examples midas9_example_forest2":click to run})}
{phang}
Fagan's plot
{phang2}
{cmd:.midas9 tp fp fn tn, es(g) fagan prior(0.20)}
{p_end}
{pmore2}
{it:({stata "midas9_examples midas9_example_fagan":click to run})}
{phang}
Likelihood Matrix
{phang2}
{cmd:.midas9 tp fp fn tn, es(g) lrmat}
{p_end}
{pmore2}
{it:({stata "midas9_examples midas9_example_lrmatrix":click to run})}
{phang}
Bivariate Boxplot
{phang2}
{cmd:.midas9 tp fp fn tn, bivbox scheme(s2color)}
{p_end}
{pmore2}
{it:({stata "midas9_examples midas9_example_bivbox":click to run})}
{phang}
Quality Assessment
{phang2}
{cmd:.midas9 tp fp fn tn prodesign ssize30 fulverif testdescr}
{p_end}
{phang2}
{cmd:refdescr subjdescr report brdspect blinded, qualib}
{p_end}
{pmore2}
{it:({stata "midas9_examples midas9_example_quadas":click to run})}
{phang}
Meta-regression
{phang2}
{cmd:.midas9 tp fp fn tn prodesign ssize30 fulverif testdescr}
{p_end}
{phang2}
{cmd:refdescr subjdescr report brdspect blinded, es(g) covars}
{p_end}
{pmore2}
{it:({stata "midas9_examples midas9_example_midareg":click to run})}
{title:Saved results}
{pstd}
{cmd:midas9} saves the following in {cmd:r()}:
{synoptset 24 tabbed}{...}
{p2col 5 15 19 2: Scalars}{p_end}
{synopt:{cmd:r(fsens)}}fixed effects estimate of summary sensitivity {p_end}
{synopt:{cmd:r(fspec)}}fixed effects estimate of summary specificity {p_end}
{synopt:{cmd:r(flrn)}}fixed effects estimate of summary likelihood ratio of a negative test {p_end}
{synopt:{cmd:r(flrp)}}fixed effects estimate of summary likelihood ratio of a positive test {p_end}
{synopt:{cmd:r(fdor)}}fixed effects estimate of summary diagnostic odds ratio {p_end}
{synopt:{cmd:r(fldor)}}fixed effects estimate of summary diagnostic score {p_end}
{synopt:{cmd:r(mtpr)}}mixed effects estimate of summary sensitivity {p_end}
{synopt:{cmd:r(mtprse)}}standard error of mixed effects estimate of summary sensitivity {p_end}
{synopt:{cmd:r(mtprlo)}}lower bound of mixed effects estimate of summary sensitivity {p_end}
{synopt:{cmd:r(mtprhi)}}upper bound of mixed effects estimate of summary sensitivity {p_end}
{synopt:{cmd:r(mtnr)}}mixed effects estimate of summary specificity {p_end}
{synopt:{cmd:r(mtnrse)}}standard error of mixed effects estimate of summary specificity {p_end}
{synopt:{cmd:r(mtnrlo)}}lower bound of mixed effects estimate of summary specificity {p_end}
{synopt:{cmd:r(mtnrhi)}}upper bound of mixed effects estimate of summary specificity {p_end}
{synopt:{cmd:r(mlrp) }}mixed effects estimate of summary likelihood ratio of a positive test result {p_end}
{synopt:{cmd:r(mlrpse)}}standard error of mixed effects estimate of summary likelihood ratio of a positive test result {p_end}
{synopt:{cmd:r(mlrplo)}}lower bound of mixed effects estimate of summary likelihood ratio of a positive test result {p_end}
{synopt:{cmd:r(mlrphi)}}upper bound of mixed effects estimate of summary likelihood ratio of a positive test result {p_end}
{synopt:{cmd:r(mlrn)}}mixed effects estimate of summary likelihood ratio of a negative test result {p_end}
{synopt:{cmd:r(mlrnse)}}standard error of summary likelihood ratio of a negative test result {p_end}
{synopt:{cmd:r(mlrnlo)}}lower bound of summary likelihood ratio of a negative test result {p_end}
{synopt:{cmd:r(mlrnhi)}}mixed effects estimate of summary likelihood ratio of a negative test result {p_end}
{synopt:{cmd:r(mdor)}}mixed effects estimate of summary diagnostic odds ratio {p_end}
{synopt:{cmd:r(mdorse)}}standard error of summary diagnostic odds ratio {p_end}
{synopt:{cmd:r(mdorlo)}}lower bound of summary diagnostic odds ratio {p_end}
{synopt:{cmd:r(mdorhi)}}upper bound of summary diagnostic odds ratio {p_end}
{synopt:{cmd:r(mldor)}}mixed effects estimate of summary diagnostic score {p_end}
{synopt:{cmd:r(mldorse)}}standard error of summary diagnostic score {p_end}
{synopt:{cmd:r(mldorlo)}}lower bound of summary diagnostic score {p_end}
{synopt:{cmd:r(mldorhi)}}upper bound of summary diagnostic score
{synopt:{cmd:r(AUC)}}Area under summary ROC curve {p_end}
{synopt:{cmd:r(AUClo)}}lower bound of area under summary ROC curve {p_end}
{synopt:{cmd:r(AUChi)}}upper bound of area under summary ROC curve {p_end}
{synopt:{cmd:r(covar)}}covariance of logits of sensitivity and specificity {p_end}
{synopt:{cmd:r(rho)}}correlation between logits of sensitivity and specificity {p_end}
{synopt:{cmd:r(rholo)}}lower bound of correlation {p_end}
{synopt:{cmd:r(rhohi)}}upper bound of correlation {p_end}
{synopt:{cmd:r(reffs1) }}variance of logit of sensitivity {p_end}
{synopt:{cmd:r(reffs1se)}}standard error of variance of logit of sensitivity {p_end}
{synopt:{cmd:r(reffs1lo)}}lower bound variance of logit of sensitivity {p_end}
{synopt:{cmd:r(reffs1hi)}}upper bound variance of logit of sensitivity {p_end}
{synopt:{cmd:r(reffs2) }}variance of logit of specificity {p_end}
{synopt:{cmd:r(reffs2se)}}standard error of variance of logit of specificity {p_end}
{synopt:{cmd:r(reffs2lo)}}lower bound variance of logit of specificity {p_end}
{synopt:{cmd:r(reffs2hi)}}upper bound variance of logit of specificity {p_end}
{synopt:{cmd:r(Islrt)}}global inconsistency index from likelihood ratio rest {p_end}
{synopt:{cmd:r(Islrtlo)}}lower bound global inconsistency index {p_end}
{synopt:{cmd:r(Islrthi)}}upper bound global inconsistency index {p_end}
{title:References}
{pmore}
Begg C.B. and Berlin J.A.
Publication bias: a problem in interpreting medical data.
J R Stat Soc A 151 (1988), pp. 419-463.
{pmore}
Chu H, Cole SR (2006).
Bivariate meta-analysis of sensitivity and specificity with sparse data:
a generalized linear mixed model approach.
Journal of Clinical Epidemiology 59:1331-1332.
{pmore}
Copas J, Jackson D.(2004)
A bound for publication bias based on the fraction of unpublished studies.
Biometrics 60:146-153
{pmore}
Deeks JJ. Macaskill P and Irwig Les.
The performance of tests of publication bias and other sample size effects in systematic
reviews of diagnostic test accuracy was assessed.
Journal of Clinical Epidemiology, Volume 58, Issue 9, September 2005, Pages 882-893.
{pmore}
Dinnes J, Deeks J, Kirby J, Roderick P.
A methodological review of how heterogeneity has been examined in systematic reviews of
diagnostic test accuracy.
Health Technol Assess 2005;9(12)
{pmore}
Fisher NI, Switzer P (1985)
Chi-plots for assessing dependence.
Biometrika 72, 253-265.
{pmore}
Fisher NI, Switzer P (2001)
Graphical assessment of dependence: Is a picture worth 100 tests?
American Statistician 55, 233-239.
{pmore}
Glas AS, Lijmer JG, Prins MH, Bonsel GJ, Bossuyt PMM (2003)
The diagnostic odds ratio: a single indicator of test performance.
Journal of Clinical Epidemiology, Volume 56, Issue 11, November, Pages 1129-1135.
{pmore}
Harbord RM, Deeks JJ, Egger M, Whiting P, Sterne JA (2006).
A unification of models for meta-analysis of diagnostic accuracy studies.
{it:Biostatistics} (online advance access).
{pmore}
Higgins JP, Thompson SG, Deeks JJ, Altman DG.
Measuring inconsistency in meta-analyses [review].
BMJ 2003;327:557-60).
{pmore}
Jaeschke R, Guyatt GH, Sackett DL.
Users' guides to the medical literature.
III. How to use an article about a diagnostic test.
B. What are the results and will they help me in caring for my patients?
The Evidence-Based Medicine Working Group.
JAMA 1994;271:703-7.
{pmore}
Lau J, Schmid CH and Chalmers TC.
Cumulative meta-analysis of clinical trials builds evidence for exemplary medical care.
Journal of Clinical Epidemiology, Volume 48, Issue 1, January 1995, Pages 45-57 )
{pmore}
Light R.J.and Pillemer D.B..
Summing up: the science of reviewing research.
Harvard University Press, Cambridge, MA (1984)
{pmore}
Rabe-Hesketh S, Skrondal A (2005).
{it:Multilevel and Longitudinal Modeling Using Stata.}
College Station, TX: Stata Press.
{pmore}
Rabe-Hesketh S, Skrondal A, Pickles A (2004).
GLLAMM Manual.
{it:U.C. Berkeley Division of Biostatistics Working Paper Series.}
Working Paper 160.
{pmore}
Reitsma JB, Glas AS, Rutjes AWS, Scholten RJPM, Bossuyt PM, Zwinderman AH .
Bivariate analysis of sensitivity and specificity
produces informative summary measures in diagnostic reviews.
{it:Journal of Clinical Epidemiology} (2005) 58:982-990.
{pmore}
Riley RD, Abrams KR, Sutton AJ, Lambert P, Thompson JR (2005).
The benefits and limitations of multivariate meta-analysis, with application to
diagnostic and prognostic studies.
University of Leicester Medical Statistics Group Technical Report Series.
Technical Report 05-04.
{pmore}
Rutter CM, Gatsonis CA (2001).
A hierarchical regression approach to meta-analysis of diagnostic test accuracy evaluations.
{it:Statistics in Medicine} 20:2865-2884.
{pmore}
Skupski DW, Rosenberg CR, Eglinton GS (2002)
Intrapartum Fetal Stimulation Tests: A Meta-Analysis.
Obstet. Gynecol. 99: 129 - 134.
{pmore}
Song F, Khan K, Dinnes J. and Sutton A.J.
Asymmetric funnel plots and publication bias in meta-analyses of diagnostic accuracy.
Int J Epidemiol 31 (2002), pp. 88-95
{pmore}
StataCorp. 2007.
Stata Statistical Software: Release 10
College station, TX:
StataCorp LP.
{pmore}
Swets JA.
Measuring the accuracy of diagnostic systems.
Science. 1988;240:1285-1293.
{pmore}
van Houwelingen H.C. , Arends L.R. and Stijnen T.
Advanced methods in meta-analysis: multivariate approach and meta-regression,
Stat Med 21 (2002) (4), pp. 589-624.
{pmore}
van Houwelingen H.C., Zwinderman K.H. and Stijnen T.
A bivariate approach to meta-analysis,
Stat Med 12 (1993) (24), pp. 2273-2284
{pmore}
Wang, MC Bushman BJ
using the normal quantile plot to explore meta-analytic data sets.
Psychological methods (1998) 3;46-54
{title:Author}
{pmore}
{browse "http://www.sitemaker.umich.edu/metadiagnosis":Ben A. Dwamena}, Division of Nuclear Medicine,
Department of Radiology, University of Michigan, USA
Email {browse "mailto:bdwamena@umich.edu":bdwamena@umich.edu} for problems, comments and suggestions
{title:Citation}
{pmore}
Users should please reference program in any published work as:
{title:Dwamena, Ben A.(2007)}
{hi: midas9: Computational and Graphical Routines for Meta-analytical Integration of Diagnostic Accuracy Studies in Stata.}
Division of Nuclear Medicine, Department of Radiology, University of Michigan Medical School, Ann Arbor, Michigan.
{title:Acknowledgement}
Thanks to
{pmore}
-Roberto Gutierrez and the Stata Development team for {help xtmelogit} and all that Stata offers....
{pmore}
-Richard Sylvester and Ruth Carlos for encouragement, suggestions and testing of {help midas9}
{pmore}
-Richard Riley for trusting me with pre-prints of his work on bivariate meta-analysis.
{pmore}
-Joseph Coveney for posting syntax for the bivariate model using {help gllamm} on Statalist.
{pmore}
-Sophia-Rabe-Hesketh and other authors of {help gllamm} for their work.
{pmore}
-Derek Wenger for assistance with coding Fagan's plot.
{pmore}
-Nick Cox for his {help polarsm} which was adapted for {opt bivbox} option in {help midas9}
and for {help mylabels}.
{pmore}
-Roger Harbord for his {help metareg}, {help metafunnel} and {help metamodbias} programs
which provided very useful ideas for {help midas9}.
{pmore}
-Mike Bradburn ( and R Harris) for {help metan} which was used to implement cumulative
and influence meta-analyses in {help midas9}.
{title:Also see}
{pmore}
On-line: help for {help metan} (if installed),
{help gllamm} (if installed),
{help mylabels} (if installed)