Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct
ContentslistsavailableatSciVerseScienceDirect
Preventive
Veterinary
Medicine
jo u r n al h om ep a ge :w ww . e l s e v ie r . c o m / l o c a t e / p r e ve t m e d
A
structural
equation
model
to
evaluate
direct
and
indirect
factors
associated
with
a
latent
measure
of
mastitis
in
Belgian
dairy
herds
J.
Detilleux
a,∗,
L.
Theron
b,
J.-M.
Beduin
b,
C.
Hanzen
baQuantitativeGeneticsGroup,DepartmentofAnimalProduction,FacultyofVeterinaryMedicine,UniversityofLiège,4000Liège,Belgium
bLargeAnimalClinics,Obstr.etpath.delareprod.deséquidés,rumin.etporcs,FacultyofVeterinaryMedicine,UniversityofLiège,4000Liège,Belgium
a
r
t
i
c
l
e
i
n
f
o
Articlehistory:Received29March2010
Receivedinrevisedform12June2012 Accepted14June2012
Keywords: Mastitis
Structuralequationmodel Latentvariable
Riskfactors
a
b
s
t
r
a
c
t
Indairycattle,manyfarmingpracticeshavebeenassociatedwithoccurrenceofmastitis butitisoftendifficulttodisentanglethecausalthreads.Structuralequationmodelsmay reducethecomplexityofsuchsituations.Here,weappliedthemethodtoexaminethe linksbetweenmastitis(subclinicalandclinical)andriskfactorssuchasherd demograph-ics,housingconditions,feedingprocedures,milkingpractices,andstrategiesofmastitis preventionandtreatmentin345dairyherdsfromtheWalloonregionofBelgium.During theperiodJanuary2006toOctober2007,upto110differentherdmanagementvariables wererecordedbytwosurveyorsusingaquestionnaireforthefarmmanagersandduringa farmvisit.Monthlysomaticcellcountsofalllactatingcowswerecollectedbythelocaldairy herdimprovementassociation.Structuralequationmodelswerecreatedtoobtainalatent measureofmastitisandtoreducethecomplexityoftherelationshipsbetweenfarming practices,betweenindicatorsofherdmastitisandbetweenboth.Robustmaximum likeli-hoodestimateswereobtainedfortheeffectsoftheherdmanagementvariablesonthelatent measureofherdmastitis.Variablesassociateddirectly(p<0.05)withthelatentmeasureof herdmastitisweretheadditionofureaintherations;thepracticesofmachinestripping, ofpre-andpost-milkingteatdisinfection;thepresenceofcowswithhyperkeratoticteats, ofcubiclesforhousingandofdirtylinersbeforemilking;thetreatmentofsubclinicalcases ofmastitis;andtheageoftheherd(latentvariableforaverageageandparityofcows, andpercentageofheifersintheherd).Treatmentofsubclinicalmastitiswasalsoan inter-mediateintheassociationbetweenherdmastitisandpost-milkingteatdisinfection.The studyillustrateshowstructuralequationmodelprovidesinformationregardingthelinear relationshipsbetweenriskfactorsandalatentmeasureofmastitis,distinguishesbetween directrelationshipsandrelationshipsmediatedthroughintermediateriskfactors,allows theconstructionoflatentvariablesandteststhedirectionalhypothesesproposedinthe model.
© 2012 Elsevier B.V. All rights reserved.
1. Introduction
Publicconcernaboutfarmanimalwelfarehassteadily grown during recent years and many indicators have been proposed to evaluate its state in terms of the 5
∗ Correspondingauthor.Tel.:+3243664129;fax:+3243664122. E-mailaddress:jdetilleux@ulg.ac.be(J.Detilleux).
freedoms,amongwhichthefreedomfromdisease(Dalmau et al., 2009). In dairy practice, disorders of the udder areamongthemostfrequentclinicalconditions encoun-tered(Fourichonetal.,2001).Forexample,itwasfound in 2 independent surveys of Belgian dairy herds that 40%of quartermilksamplesfromsubclinicallyinfected cowscontainedmastitispathogens(Detilleuxetal.,1999;
Piepers etal., 2007).Given this highprevalence,
scien-tists have searched for and identified a great number 0167-5877/$–seefrontmatter © 2012 Elsevier B.V. All rights reserved.
Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct of risk factors for the developmentof clinical mastitis.
Theseincludefactorsattheherd,cowandquarterlevels
(Breenetal.,2009).
In this study, we restricted ourselves to the study of factorsat theherd level. Factorssuch asinadequate nutrition,poormilkinghygiene,deficientmilking proce-duresorincreasedexposureoftheherdtoenvironmental pathogensmayincreasetheriskofclinicalandsubclinical mastitis(deVliegheretal.,2004;Haltiaetal.,2006;Nyman
etal.,2007;Schukkenetal.,1991).Butallthese
characteris-ticsareinterrelatedsoitisdifficulttodistinguishbetween spuriousandfactualassociations,orbetweendirectand mediatedeffects. To reducethe complexity ofsuch sit-uations,it ispossibletousestructural equationmodels (SEM) with latent variables (Bollen, 2002).Within this methodology,observedvariablesmaybeconsideredasthe expressionofasmallnumberoflatentconstructsthat can-notbedirectlymeasuredbutareinferredfromtheobserved variables.Inoursetting,thiswouldsuggestthatobserved herdcharacteristicsandmastitisindicatorscanbe aggre-gatedinafewnumbersofunderlyingconcepts.Then,the covarianceorcorrelationmatrices(orboth)betweenlatent constructsandobservedvariables,andbetweenlatent con-structs,aremodeledasafunctionofasetofparameters.It isthenpossibletotest alternativehypothesesaboutthe relationshipsbetweenthesevariables.Forexample, rela-tionshipsbetweensomaticcellcountsandmilkyieldhave beenexploredwiththismethod(delosCamposetal.,2006; Wuetal.,2008).TheSEMhandlescollinearityamong inde-pendentvariablesandcontrolsspuriousinflationoftypeI errorwhichconstitutesariskinmultipleunivariate anal-yseswhentestingcomplexrelationships(Pugesek,2003). AnotherinterestingfeatureoftheSEMconsistsinthe con-jointestimationofdirectandmediated(orindirect)effects
(Casal et al., 1990). Here, a direct effect will occurif a
putativeriskfactorinfluencesdirectlyonmastitis.Itisnot passedonthroughinterveningvariablesbutremainswhen allothervariablesinthemodelareheldconstant.Onthe otherhand,amediatedeffectwilloccurwhentheinfluence oftheriskfactoronmastitisisthroughone(ormore) inter-veningvariable.IfwedenoteYasthestateofmastitis,Xas theriskfactorandMastheinterveningvariable,thenthe pathX→M→YrepresentsthemediatedeffectbywhichX indirectlyaffectsYthroughM.Totaleffectsarethesumof directandmediatedeffects.Thecomparisonofdirectand mediatedeffectsmightallowustosubstituteintervening variablestomeasuresofmastitiswhenthesearedifficultto obtainoratahighcost.Thiscouldbethecaseifatreatment (X)wasclearingabacterialinfection(Y)bymodifyingsome biochemicalmilkprofile(M).Thisexampleillustrateshow itcouldbemorecost-effectivetoevaluatetheeffectofa treatmentbymeasuringthevariationofmilkcomponents bymodernrapidanalyticalmethods(M)thanbycounting coloniesonmicrobiologicalcultures(Y).Theidentification ofinterveningvariablesmayservealsotoclarifythenature oftherelationshipsbetweenmastitisandriskfactor.This issuereceivedrenewedinterestasawaytoaddressthe crit-icismsof‘blackbox’epidemiology(HafemanandSchwartz,
2009).
Theobjectiveof this paperis thustoapplytheSEM methodologytoevaluateand toquantifythedirectand
mediatedeffectsofherdcharacteristicsonmastitisindairy herdsfromtheWalloonregionofBelgium.
2. Materialsandmethods 2.1. Animalsandstudyarea
A random stratified sample of 349 dairy farms was surveyedbetweenJanuary2006andOctober2007inthe WalloonregionofBelgium.Thissamplerepresented25% ofproducersregisteredfornationalmilkrecording,fora totalof16,000cows.Asaruleofthumb,thesamplesize inSEMshouldbe10–20timesthenumberofexploratory variables,withaminimumof200(Hoe,2008).The strati-ficationwasbasedontheresultsofaprincipalcomponent analysisofthemanagementandherdcharacteristicsofall dairyherdspresentintheregion(n=1303).Thefirsttwo principal componentsweredividedinquartiles andthe herdswererandomlysampledwithineachofthese quar-tiles(16differentstrata)toensureallfarmcharacteristics wererepresented.
Up to110 differentfarming practices and indicators ofmastitiswererecordedineachfarmbytwosurveyors. Aquestionnairewasdesignedtocollectinformation dur-ingtheinterviewwiththefarmer,usingclosedquestions
(Delfosse et al.,2008). Farming practices includedherd
demographics(n=5),productiveandreproductive indica-tors(n=4),feedingprocedures(n=16),typesofhousing (n=12),strategies of mastitisprevention andtreatment (n=48),and milkingmethods(n=19).Sixdifferent indi-catorsofmastitiswereconsideredbasedonSCCbecause information on bacteriological findings and on clinical casesofmastitiswasnotobtainable.Theseindicatorswere ‘3-moSCC’,‘cowsactually withhighSCC’(numbersand percentages),‘cowspreviouslywithhighSCC’,‘lastSCC’, and‘cowsmilkedaside’.TheyaredescribedinTable1.
2.2. Statisticalanalysis
AfterageneralintroductiontoSEM,thestatistical anal-ysesforourspecificstudyarepresented.Theyconsisted intheidentificationofnoteworthyassociationsbetween mastitisindicatorsandfarmingpractices,thepreparation ofthedatafortheSEM(imputationandfactoranalysis),the establishmentoftheSEMitself(measurementand struc-turalsubmodels),andfinallytheestimationofthedirect, mediatedandtotaleffects.
2.2.1. IntroductiontoSEM
ASEMiscomposedoftwodifferentcomponents.The firstcomponentisthestructuralsubmodelwhere endoge-nous latentvariables areregressed onlatent predictors accordingto:
=B++,
whereisavectorofendogenouslatentvariables,isa vectorofexogenouslatentvariablesand isavectorof errorterms.Themodelcontrastsexogenous(i.e., indepen-dentfromthestatesofothervariables)fromendogenous variables.ItisfurtherassumedE()=,var()=,E()=0,
Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct
Table1
ShortdescriptionofindicatorsofhighSCCandpotentialriskfactorsnoteliminatedafterthepreliminaryunivariateanalyses.
Indicators Recording Descriptionandclassification
Somaticcellcounts
LastSCC DHI-records Log-transformedherdsomaticcellcount(SCC)atlastrecordingbeforethe
visit(log2(SCC/100,000)+3,whereSCCarecounts/ml)
3-moSCC DHI-records Arithmeticaverageoverthelast3monthsbeforethevisitoflog-transformed
herdSCC(log2(SCC/100,000)+3,whereSCCarecounts/ml)
CowsactuallywithhighSCC DHI-records Percentageandnmberofcowswith≥1monthlysample≥400,000cells/mlin thecurrentlactation
CowspreviouslywithhighSCC DHI-records Numberofcowswith≥1monthlysample≥400,000cells/mlintheprevious lactation
Cowsmilkedaside Visual/interview NumberofcowstreatedwithantibioticsandcowswithhighSCCforwhich
milkwasnotincludedinthetank
Herddemographics
Heifers DHI-records Percentageofnonlactatingprimiparouscows
Age DHI-records Arithmeticaverageageinmonthsofcowspresentatthefarmvisit
Parity DHI-records Arithmeticaverageparityofcowspresentatthefarmvisit
Lactatingcows DHI-records Numberoflactatingcows
Drycows DHI-records Numberofdrycows
Productiveindicators
Milk DHI-records Arithmeticaveragetest-daymilkoflactatingcowspresentatthefarmvisit
Milkfat DHI-records Arithmeticaveragetest-daymilkfatpercentageoflactatingcowspresentat
thefarmvisit
Milkprotein DHI-records Arithmeticaveragetest-dayproteinpercentageoflactatingcowspresentat
thefarmvisit
Milkquota DHI-records Totalintonnesoftheherdmilkquota
Milkingmethods
Preparationtime Visual/interview Timeinsecondsnecessarytopreparetheudderbeforemilking
Delay Visual/interview Timebetweentheendoftheudderpreparationandtheinstallationofthe
milkingmachine(s)
Handwashing Visual/interview Whetherornotmilker(s)washed(ornot)theirhandsaftermilkingeachcow
Milker Visual/interview Whetherornotonepersonmilkedthecows
Teatspre-dipping Visual/interview Whetherornotmilker(s)disinfectedteatsbeforemilking
Foremilkcheck Visual/interview Whetherornotmilker(s)examinedforemilkofeachquarterofeachcowprior
tomilking
Machinestripping Visual/interview Whetherornotmilker(s)appliedpressureontheclawattheendofmilkingto removepartofresidualmilk
Siliconelinertype Visual/interview Whetherornotlinersofthemilkingmachinewereinsilicone
Dirtyliner Visual Whetherornotlinersweredirtyinsideatthebeginningofmilking
Pulsatortype Visual/interview Whetherornotpulsatorwasusedperclaw
Hyperkeratosis Visual Percentageofcowswithlesion(s)ofhyperkeratosis
Clawspermilker Visual Numberofclawspermilker
Typesofhousing
Calvingpen Visual/interview Whetherornotthefarmhadapeninwhichcowsmaycalve
Cubicles Visual/interview Whetherornotlactatingcowswerehousedinafree-stalloncubicles
Gratedfloor Visual/interview Whetherornotlactatingcowswerehousedongratedfloor
Insidebarn Visual/interview Whetherornotlactatingcowswerehousedinsidebarns
Mastitispreventionandtreatment
Partialinsertion Visual/interview Whetherornotcowsreceivedantibioticswithashort(<4mm)orlong (>54mm)infusioncannulaatdrying
Treatmentifsubclinicalmastitis Visual/interview WhetherornotcowswithSCCabovethresholdand/orpositiveCMTwere infusedwithantibiotics
Treatmentifclots Visual/interview Whetherornotuddersofcowswithclotsinmilkwereinfusedwithantibiotics Treatmentifswelledudder Visual/interview Whetherornotcowswithswelledudderreceivedantibiotics(systematicand
intra-mammaryadministration)
Treatmentifbadstate Visual/interview Whetherornotcowswithclinicalmastitis(badgeneralstate)received antibiotics(systematicandintra-mammaryadministration)
Uddercleaning Visual/interview Whetherornotmilker(s)cleanedudderteatswithadryorhumidtissue
(paperorcloth)
Cupwashing Visual/interview Whetherornotmilker(s)washedthecupsofcowswithsubclinicalorclinical
mastitis
Teatspost-dipping Visual/interview Whetherornotmilker(s)disinfectedsystematicallyteatsbeforemilking
Dryperiod Interview Timeindaysofthedryperiod
Feedingprocedure
Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct
η
1y
1 λy 11ν
1y
2 λy 12ν
2y
3 λy 13ν
3η
2y
4 λy 24ν
4y
5 λy 25ν
5y
6 λy 26ν
6β
12ξ
1x
1 λx 11ε
1x
2 λx 12ε
2γ
11γ
12ζ
1ζ
2Fig.1.Anexampleofastructuralequationmodelwith2endogenouslatentvariables(1and2),oneexogenouslatentvariable(1)and8observed
variables(y1toy3,y4toy6,x1andx2).Inthemeasurementsubmodel,regressioncoefficientsrelateobservedandlatentvariables(x11,x12,andy11toy26).
Inthestructuralsubmodel,directlinksbetweenlatentvariablesarerepresentedbytheregressioncoefficientsˇ12,11and21.Errorsarerepresentedby
thesymbols,,and.Seethetextformoredetails.
var()=,andcov(,)=0.MatrixBcontainsrecursiveand simultaneouseffectsrelatingelementsof,andcontains regressioncoefficientsbetweenand.Equivalently,the structuralmodelcanbewrittenas:
=(I−B)−1+(I−B)−1.
ThesecondcomponentoftheSEMcontainsthe mea-surementsubmodelsthatlinkthevectorfortheobservable exogenous(x)andendogenous(y)variablestotheir under-lying(latent)variables:
y-measurementsubmodel: y=y+,
x-measurementsubmodel: x=x+,
with E(
)=0, var()=y, E()=0, var()=x andcov(
,)=0.Thus,theelementsofxareindicatorsofthe elementsofandtheelementsofyareindicatorsofthe elementsof. Ifx=I and=0,thenx=.Similarly, ify=Iand
=0,theny=.Combining the equations of the SEM, the y-measurementmodelcanberewrittenas:
y=x␦,
where =y(I−B)−1−1
x and ␦=y(I−B)−1[− −1x ]+.Through the matrix , a SEM providesa
wayofinterpretingtherelationshipbetweenobservable variables(x,y)asafunctionofregressionparametersof structural(Band)andmeasurement(xandy)
sub-models.Furthermore,theSEMreducestoa multivariate
multipleregressionmodelwhenB=0,andxandyare mea-suredwithouterror(i.e.,y= x+).Fig.1showsthepath diagramforahypotheticalSEM.
Whennodistinctionisdonebetweenexogenousand endogenous variables, we obtained the so-called ‘all-y’ notationforbothcomponentsoftheSEM: =+for thestructuralsubmodelandz=+forthe measure-mentsubmodel,with:
=
, = 0 0 V , var()= 0 0 , z= x y , = x y , and var()= x 0 0 y . Thematrix representsthedirecteffects between ele-ments of .The mediated effects are 2 and the totaleffectsare+2.
2.2.2. Identificationofnoteworthyassociations
AfteraBox–Coxtransformationofthecontinuous vari-ables that werenot normally distributed, we applied a batteryofunivariateanalyses(correlation,chi-squareand F-tests)andidentified that,outofall104farming prac-tices,35werepotentiallyassociated(p≤0.10)witheach otherandwithatleastoneofthe6indicatorsofmastitis. Thesevariableswerekeptforthefollowinganalysesand aredescribedinTable1.
Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct 0 5 10 15 20 25 30 35 40 20 15 10 5 0 Eigenvalue of factor Number of factors
Fig.2. Screeplotforthefirst20factorsextractedfromthedata.
2.2.3. Multipleimputationandfactoranalysis
Missingdatawereimputed.TheMarkovchainMonte Carlo (MCMC) method algorithm was used to create 5 independent draws of missing data from multivari-ate normal distributions, and these draws were then averaged. The starting values for the MCMC algorithm wereposterior modes ofdistributions generated bythe expected-maximizationalgorithmfromuninformative Jef-freys prior (procedures MI and MIANALYZE of SAS®).
Averages of imputed categorical data were rounded to thenearestintegervalue.Simulationstudiesondatawith binaryandordinalvariablesshowedresultsusingmultiple imputationbasedonthemultivariatenormaldistributions werenotlessrobustthanthosebasedonthemore flex-iblefullyconditionalspecification(LeeandCarlin,2010). However, dataon4 farmshad tobediscardedbecause informationonallvariablescollectedtodescribethetypes ofhousingwaslacking.
Next,weperformedafactoranalysistoidentifywhether factorswerecontributingtothecommonvarianceinthe 41variablesmeasuringmanagementpracticesandmastitis (procedureFactoronSAS®).Variableswerenot
standard-izedfortheanalysisandthemaximumlikelihoodmethod waschosentoestimatefactorloadings,withsquared mul-tiple correlationofeach observed variableregressedon alltheothersasthepriorcommunalities.Theresults sug-gestedthat18outofthe41variablescouldbegroupedinto 5differentfactors.Indeed,the5thfactorwasthefirstone tohaveaneigenvaluebelow1anditcorrespondedtothe pointatwhichthecurvestartedbendingonthescreeplot (Fig.2).Theproportionofthecommonvarianceexplained bythe5factorswasgreaterthan80%.
Variablesofthese5factorsthathadloadings>0.3were consideredinthelatentvariablesoftheSEM(seebelow: measurementsubmodel).ThefirstlatentvariablewasAGE regrouping theobserved variables ‘Parity’, ‘Heifers’,and ‘Age’;thesecondonewasPRODregroupingthevariables ‘Milk’,‘Milkprotein’,‘Milkfat’,and‘Milkquota’;thethird wasNUMregrouping thevariables ‘Lactatingcows’ and ‘Drycows’;thefourthonewasMLKregroupingthe vari-ables‘Preparationtime’,‘Delay’,and‘Handwashing’;and thelastonewasMAMregrouping‘3-moSCC’,‘Numberof cowsactuallywithhighSCC’,‘Numberofcowsalreadywith
highSCC’,‘PercentageofcowsactuallywithhighSCC’,‘SCS atlastrecording’,and‘Numberofmilkedasidecows’.The remaining23variables wereconsideredasindependent riskfactorsintheSEM.
2.2.4. Identificationofthemeasurementsubmodels Themeasurement submodel indicates howobserved variablesarelinkedtounderlyinglatentvariables.Using thesimple‘all-y’notation,all41observedvariables(z1to
z41)wererelatedto28latentvariables( 1to 28),with
1=MAMregroupingz1toz6, 2=AGEregroupingz7 to
z9, 3=PRODregroupingz10toz13, 4=NUMB
regroup-ingz14toz15, 5=MLKregrouping z16toz18,and 6 to
28aretheerror-freelatentvariablesforthe23remaining
riskfactors,i.e.,consideringz19toz41arerandomvariables
contaminatedbyerrors(19to41).Modelsfor 2
(vari-ableAGE)and 25 (=variable‘Dirtyliners’)aregiven as
examples:
z7 z8 z9 = 1 8 9 [ 2]+ 7 8 9 and z25= 25+25,withz7=‘Averageage’inmonths,z8=‘Averageparity’,and
z9=‘Percentageofheifers’.Thevalueof8 indicatesthe
extenttowhichz8dependsonAGE( 2),inunitsgivenby
thereference,chosenheretobez7.Theprocedurewas
sim-ilarforMAM(unit=somaticcellscore),PROD(units=kg milk),NUMB(units=numberoflactatingcows),andMLK (units=timeinsecondstopreparetheudder).Fixingone loadingisrequiredtoidentifytheparametersofthemodel. Anotherconstraintwouldconsistinfixingthevarianceof thelatentvariablealthoughSteiger(2002)arguedthislast constraintcaninteractwithothermodelconstraintsand interferewithsomehypothesistesting.Squaredmultiple correlationsbetweenlatentandeveryobservedvariable, denotedR2,wereusedtodeterminetheextenttowhich
theobservedvariableadequatelymeasuresitsrespective underlyingconstruct.
2.2.5. Identificationofthestructuralsubmodels
Structuralsubmodelsindicatehowlatentvariablesare linkedtoeachother.Thepremises forconstructingthis partof theSEM werethat all 27 latentvariables could affectMAMandbethemselvesaffectedbylatentvariables otherthanMAMandthemselves.Thenforthemthlatent variable,wehave: [ m]= [ m,1 m,2 m,3 ... m,28]·
⎡
⎢
⎢
⎢
⎢
⎣
1 2 3 . . . 28⎤
⎥
⎥
⎥
⎥
⎦
+[ωm] with m=1–28Values for m,1 and m,m werefixed to0 for m=1–28.
Weassigned(inthetextbelow)thesymbolRFMAMtothe
latentvariables forwhich partialregression coefficients with MAM (1,2, 1,3,..., or 1,28) were significantly
different from null (p<0.05). Having identified these RFMAM,wedenotedasRF,thelatentvariablesforwhich
Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct partialregressioncoefficients(m,2,m,3,...,orm,28with
m=2–28) with RFMAM were significantly different from
null(p<0.05).VariablesotherthanRFMAMandRFwerenot
includedinthefinalmodel.Thedirectionofthese relation-ships(fromRFtoRFMAMtoMAM)wasbasedonourcurrent
knowledgeofmastitis.Wemaythinkattheprocedureasa classicalbackwardstepwiseregressionanalysisbut,here, wewentfurtherbydeterminingwhethertheRFMAMkept
attheend ofthebackward procedurewere themselves influencedbyRFvariables.
Thefinaltheoreticalmodelis:
MAM= n
k=1 1,kRFMAMk +ω1 with n≤28, and RFMAMm = nm k=1 m,kRFm+ωm for m=1,...,n.2.2.6. Estimationoftheparametersandfitofthemodels Parameters of the final SEM were estimated with the“robust”maximumlikelihoodmethod(Boomsmaand
Hoogland,2001).Inthismethod,alsocalledthemaximum
likelihood–meanadjusted,parametersareestimatedby maximumlikelihood and standard errors areestimated fromtheasymptoticcovarianceandcorrelationmatrices. These“robustestimators”aresupposedtobemorerobust againstviolationsoftheassumptionsoflargesamplesize andnon-normalitythan regularestimators(Satorra and
Bentler,1988).Thematrices werebasedonthePearson
correlations for continuous variables and on the tetra-choricandthepolychoriccorrelationsforordinalindicators (LISREL®program2.8,JöreskogandSörbom,1996).
Afterthemodelparameterswereestimated,thedegree towhichthemodelfitsthedatawasassessed.Fitindices, allprovidedbyLISREL,canbeclassifiedintoseveralclasses thatinclude (1) discrepancy functions,suchasthe root mean square error of approximation (RMSEA=squared averagedifferencesbetweenobservedandmodel-implied covariances),(2)teststhatcomparethetargetmodelwith thenullmodel,suchasthecomparativefitindex(CFI)or thenormedfitindex(NFI),(3)informationtheorygoodness offitmeasures,suchastheAkaikeInformationcriterion (AIC),and(4)noncentralityfitindices.AnRMSEAvalueof lessthan0.08suggestssatisfactoryfit,andavalueofless than0.05suggestsclosefit(BrowneandCudeck,1993).The indicesNFIandCFI,allnormallylieintherange0.0–1.0, withhighervalues indicatingbetterfit. Asa benchmark for good fit, the value0.90 is oftenused (Kline, 2005). Inadditiontoomnibusgoodness-of-fitmeasures(RMSEA, CFI,NFI,AIC),nullhypothesesthatindividualparameters oftheSEMaredifferentfromzeroweretestedthrough inspectionof the Waldstatistic (labeled t-value in LIS-REL),modificationindices(estimatesofthechangeinthe likelihood-ratio chi-squarestatisticfor themodel if the parameterisspecifiedasafreeparameter),and standard-izedresiduals(Bollen,1989;Kline,2005).Estimatesofthe parameterswereobtainedasifthevariancesofthe vari-ableswereunity(completestandardizationinLISREL).
2.2.7. Total,directandindirecteffects
Thelaststepintheanalysesconsistedindetermining, forthefinalSEM,thedirect,mediatedandtotaleffecton MAM.Usingthenotationpresentedintheintroduction,X istheriskfactororRFMAM,YistheMAMandMisan
inter-mediateriskfactorinthepathwayfromXtoY.Thedirect effectsofXonYwereestimatedbythecorresponding ele-mentsofthematrix,i.e.,partialregressioncoefficients. Themediatedeffectswereobtainedfrom2,asthe
prod-uctoftheestimatedregressioncoefficientofXonMtimes theestimatedregressioncoefficientMonY.Themediated effectofXonYcanalsobeestimatedbystandardregression methods,asthedifferencebetweenestimatedregression coefficientofXonY(X→Y)andestimateddirecteffectofX onY(X|M→Y).Thetwomethodswillleadequivalent esti-mateswhennolatentvariableisused,nodataismissing andcovariatesarethesameinallequations.Asimulation studyillustratedthesuperiorityofSEM(Iacobuccietal., 2007).TheSobeltest(Sobel,1982)wasusedtotestthe nullhypothesisthatthemediatedeffectisnull.
3. Results
DescriptivestatisticsaregiveninTable2forthe345 farmsusedintheanalyses.Theaveragenumberoflactating cowswas50perherd,rangingfrom15to165.Theaverage numberofheiferswas6perherdandrangedfrom0to30. Milkquotavariedfrom105to1380tonnes,withanaverage of378tonnes.Farmsomaticcellscoreatlastcheckranged from1.60to5.20andtheaverageoverthelast3months from2.85to3.89.Managementpracticesdifferedbetween farmsbutthemajorityofproducersfollow recommenda-tionstopreventmastitis:theycheckedforemilkforearly signsofinfection(78%),cleanedtheudderbeforemilking (78%),practisedpost-milkingteatdisinfection(64%)and mostofthemtreatedcowswithclinicalmastitis(>90%). Theydippedteatsbeforemilking(7%),strippedmachine (37%)andwashedthecups(34%).Onaverage,20%of sam-pledcowspresentedsignsofhyperkeratosisandonly29% offarmshadcowswithoutsignsofit.
Completelystandardizedestimatesoftheparameters of the final SEM are given in Table3 for the measure-mentandinFig.3forthefinalstructuralsubmodels.The goodness-of-fit statistics (RMSEA<0.01; NFI=0.95, and CFI=1.0)suggestedclosefitofthefinalmodel.InTable3, we see that 66% of the variance in the average parity number(z8)isexplainedbythelatentvariableAGE( 2).
Theestimated valuefor8 is 0.81 meaningthatz8 will
increase by 0.81 in terms of standard deviations when AGEincreasesbyonestandarddeviation.The‘t-value’of 20.4suggests8 exceedsthecriticalvalueof2.58atthe
significance level of 1% (p<0.01). Parity was positively associatedwiththeunderlyingAGEandthecoefficientfor thepercentageofheiferswas,logically,negative.Looking at MAM, thestandardized coefficients showedthatSCC at last check and animals with high SCC(number and percentage)weremorehighlycorrelatedwithMAMthan cowsmilkedaside.ThevariableMLKwaspositivelyrelated withthetimenecessarytocleantheudderbeforemilking andthepracticetowashhandaftermilking.Finally,herd
Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct
Table2
Percentageofherdscharacterizedbythepresence(vs.absence)ofabinaryriskfactor(percent);meanandstandarderror(SE)forquantitativeriskfactor; averageof3-moSCCforherdswith(yesherds)orwithout(noherds)theriskfactor;percentageofherdswithnoinformationontheriskfactor(Pmiss).
Riskfactors Mean(SE) Percent Yesherds Noherds Pmiss
IndicatorofhighSCC
3-moSCC 3.40(0.01) 0.0
CowsactuallywithhighSCC 13.76(0.44) 2.3
CowspreviouslywithhighSCC 6.18(0.25) 2.3
Cowsmilkedaside 1.70(0.11) 0.3
LastSCC 3.22(0.03) 2.3 Herddemographics Heifers 33.03(0.53) 2.3 Age 52.65(0.36) 2.3 Parity 2.65(0.02) 2.3 Lactatingcows 50.48(1.19) 0.0 Drycows 6.16(0.26) 1.4 Productiveindicators Milk 24.12(0.28) 2.3 Milkfat 4.06(0.02) 2.3 Milkprotein 3.33(0.01) 2.3 Milkquota 377.99(10.5) 2.6 Milkingmethods Preparationtime 12.39(0.70) 0.6 Delay 75.17(4.18) 0.6 Handwashing 41.2 3.40(0.01) 3.39(0.01) 2.6 Milker 24.6 3.39(0.02) 3.42(0.03) 0.1 Teatspre-dipping 7.0 3.46(0.04) 3.40(0.01)* 0.3 Foremilkcheck 78.0 3.41(0.01) 3.37(0.02) 0.0 Machinestripping 37.4 3.43(0.02) 3.38(0.01)* 0.3
Siliconelinertype 13.0 3.39(0.03) 3.40(0.01) 0.0
Dirtyliner 7.8 3.51(0.03) 3.39(0.01)* 0.3
Pulsatortype 19.1 3.43(0.03) 3.39(0.01) 0.6
Hyperkeratosis 19.62(0.83) 8.3
Clawspermilker 6.64(0.17) 0.9
Housing Calvingpen 34.8 3.36(0.02) 3.42(0.01) 3.5 Cubicles 45.2 3.37(0.01) 3.43(0.01)* 1.1 Gratedfloor 47.5 3.38(0.01) 3.41(0.01) 1.1 Insidebarn 85.8 3.40(0.02) 3.42(0.03) 1.1 Mastitistreatment Subclinicalmastitis 27.8 3.40(0.02) 3.40(0.01) 1.1
Ifpresenceofclotsinmilk 61.2 3.38(0.04) 3.40(0.01) 0.0
Ifswelledudder 93.3 3.40(0.01) 3.41(0.07) 0.3
Ifbadgeneralstate 94.2 3.39(0.02) 3.40(0.01) 1.4
Mastitisprevention Partialinsertion 55.6 3.41(0.01) 3.39(0.01) 0.0 Uddercleaning 78.5 3.39(0.01) 3.44(0.02) 0.0 Cupwashing 33.9 3.39(0.02) 3.41(0.01) 0.9 Post-dipping 64.1 3.38(0.01) 3.44(0.02)* 0.3 Dryperiod 50.05(0.49) 0.1 Feedingprocedure Ureainfeed 10.4 3.46(0.03) 3.39(0.01) 1.7
*Significantdifferencebetweenyesandnoherds(t-test;p<0.05).
average production was strongly associated withPROD contrarytofatandproteinpercentages.
Forthestructuralsubmodel(Fig.3),completely stan-dardized coefficientsshowedthat AGE,additionofurea in the rations, presence of dirty liners, machine strip-ping, presence of cows with hyperkeratosis, pre- and post-milking teat disinfection, treatment of subclinical casesofmastitisandhousingofmilkingcowsoncubicles are directly correlated with MAM. The estimates were negativewhenhyperkeratoriccowswereobservedinthe farm,whenfarmersdisinfectteatsaftermilkingandwhen
lactating cows were housed in a free-stall on cubicles, andpositivefortheothers.Someoftheriskfactorwith significant links with MAM were also associated with othervariables,forexamplewithMLK(post-milkingteat disinfection,dirtyliners),withNUMB(hyperkeratosisand machine strip),or withboth PROD and NUMB(urea in feed,cubicles,dirtyliners,AGE).Treatmentforsubclinical mastitis and post-dipping were positively associated. Variables such as partial insertion, foremilk check and uddercleaning wereassociated withMLKbut not with MAM.
Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct PROD 0.15 (0.02) 0.41 (0.01) -0.04(0.01) -0.08 (0.02) 0.07(0.02) 0.09 (0.01) Presence of hyperkeratosis MAM Pre-milking teat disinfecon Machine stripping Urea in feed MLK Dirty liners Treatment of subclinical mastitis Foremilk check Partial insertion Udder cleaning Post-milking teat disinfecon AGE NUMB Cubicles 0.06 (0.02) 0.13 (0.03) 0.18(0.03) -0.12 (0.02) 0.13 (0.03) 0.10 (0.04) -0.07 (0.02) -0.05(0.02) 0.31 (0.04) 0.01 (0.00) 0.07(0.01) 0.09(0.02) -0.10 (0.00) 0.09 (0.002) 0.05 (0.01) 0.12 (0.02) 0.13 (0.02) 0.05 (0.01)
Fig.3.Finalstructuralmodeldescribingthedirect(straightline)andindirect(dashedline)linksbetweenthelatentstateofudderhealth(MAM)andrisk factors.Seethetextformoredetails.
Direct and mediated relationships were observed in theassociation‘post-milkingteatdisinfection–treatment of subclinical mastitis – MAM’ (Fig. 3), in which treat-mentof subclinicalmastitiswasanintermediate in the pathwayfromteatdisinfectiontoMAM.Thepartofthe totalassociation(−0.11SCS;SE=0.02)betweenMAMand teat disinfectionthat was mediated throughsubclinical treatmentwasestimatedat+0.01 SCS(SE=0.003).And, althoughthismediatedeffectwassmall,itwassignificantly differentfromnull(p<0.05).
4. Discussion
Among the numerous reports on the relationships betweenherdcharacteristicsandmastitis,thisoneis par-ticularin that it approachedmastitis asa composite of severalcontributoryindicators,representedbyMAM.The MAMcanbeunderstoodasaherdvariableevaluatingherd mastitisthatisonlyobservedthroughmultipleindicators, eachcapturingdifferentaspectsofit.Statementsaboutthe associationsbetweenMAMandriskfactorsaretherefore morecomprehensiveandlessspecificthanthosemadefor eachindividualmastitisindicator.Themethodologyisnot adequatetofindmanagementstrategieseffectiveagainst particularmammarypathogensbutitissuitedtostudies, likeours,withtheobjectiveofidentifyingfactors influenc-ingherdmastitisinaglobalmanner,giventhattrendsin
mastitishavechangedoverthelast50yearsandthat differ-entmastitispathogensarepredominantindifferentherds, regionsandcountries(ZadoksandFitzpatrick,2009).
Lookingatthecompletelystandardizedregression coef-ficients,allexpressedin unitsof standarddeviation,we observedthemostinfluentialvariableonMAM wasthe presence vs.absenceofdirtyliners ( 25).Indeed, MAM
increasedby0.18(SE=0.03)whenlinersweredirty(Fig.1). Thepresencevs.absenceofdirtylinerswasitselfincreased by 0.05 (SE=0.01) when NUMB increased by one stan-dard deviation. Among other RFMAM with standardized
direct effectsonMAM greaterthan0.10, wealsofound dietary urea (+0.13, SE=0.03) and the practice of pre-dipping(+0.13,SE=0.03).Note,however,thatcontroversial reportswereretrievedintheliteratureasinSterketal.
(1978)whoobservedapositiverelationshipbetweenurea
andmastitisandinErbetal.(1976)inwhichnorelationship wasdiscovered.
Thepracticeofpost-milkingteatdisinfectionwas nega-tivelyassociatedwithMAM,withadirectstandardizedlink of−0.12(SE=0.02).Thiswasexpectedgiventhenumerous previousstudiesthatdemonstratedthebeneficialimpact ofpost-milkingteatdisinfectiononclinicaland subclini-calmastitis(Barkemaetal.,1998).But,thepracticewas alsoassociatedwithMAMthroughitslinkwiththe vari-able‘treatmentforsubclinicalcase’.Thismediatedeffect was estimated at +0.01 (SE=0.00) and wasin opposite
Please cite this article in press as: Detilleux, J., et al., A structural equation model to evaluate direct
Table3
Measurementmodelsforthefinalstructuralequationmodel:robust max-imumlikelihoodestimate(withthestandarderrorsinparentheses)ofthe effectsoneachlatentconstruct(AGE,PROD,MAM,MLK,andNUMB)along withthe‘t-value’(Waldstatisticwithcriticalvalueof2.58atp<0.01 sig-nificancelevel)andthesquaredmultiplecorrelation(R2).Seethetextfor
moredetails.
Estimate(SE) ‘t-Value’ R2
AGE Parity 0.81(0.04) 20.39 0.66 Heifers −0.60(0.10) −6.54 0.36 Age 1(ref) PROD Milkprotein −0.06(0.01) −13.9 0.00 Milfat 0.02(0.01) 3.37 0.00 Quota 1(ref) Milk 0.27(0.12) 2.31 0.09 MAM 3-moSCC 1(ref)
CowsactuallywithhighSCC 0.46(0.02) 22.19 0.25
CowsactuallywithhighSCC(%) 0.55(0.02) 21.90 0.35 CowspreviouslywithhighSCC 0.46(0.04) 12.63 0.25
Cowsmilkedaside 0.24(0.02) 14.72 0.07
LastSCC 0.71(0.03) 21.90 0.76
MLK
Delay 0.46(0.04) 5.98 0.20
Handwashing 0.24(0.04) 5.44 0.04
Preparationtime 1(ref)
NUMB
Lactatingcows 1(ref)
Drycows 0.21(0.08) 2.80 0.07
directiontothedirect link,sotheestimatedtotaleffect
wasestimatedat−0.11(SE=0.02),lowerthanthedirect
effect.Eveniftheyarenotspectacular,theseresults
illus-trate thepotentialimportanceofdecomposingthetotal
relationshipintoitsdirectandindirectcomponents.For
example,ifthemediatedlinkhadbeengreaterthanthe
directlink,post-dippingwouldhavebeenincorrectly
asso-ciatedwithnomastitisbystandardregressiontechniques
althoughitstotaleffectwouldhavebeennotprotective.
OtherRFMAMhaddirectstandardizedeffectslowerthan
0.10. Forexample,MAM waslowerin farmsthathouse
lactatingcowsinwinterinatie-stall(−0.08,SE=0.02)
sim-ilarlytotheassociationfoundwithlowclinicalmastitis
incidence(KjæstadandSimensen,2001)andherdaverage
SCC(Kösteretal.,2006).ThelatentvariableAGEhada
pos-itiveeffectonMAMlikeinotherstudiesthatshowedan effectofincreasinglactationnumberonSCC(Busatoetal., 2000).Anotherexamplewastheslightnegativeassociation betweenthepresenceofhyperkeratosisandMAM.Others foundsevereteatlesionsisassociatedwithincreasedrisk ofclinicalmastitisandhigherSCC(Neijenhuisetal.,2001). Conversely,Gleeson(2004)foundnocorrelationbetween teathyperkeratosisscoreandSCCwhenteatswere disin-fectedaftermilking.
Somelatentvariables,suchasPRODandNUMB, influ-encedMAMonlyindirectly,throughtheirlinkswithother interveningvariables.Forexample,theyinfluencedMAM through theireffectonthepresence ofcubicles. Inthis survey,farmsthathouselactatingcowsinwinterina tie-stallwereindeedlargerandhadagreatermilkquota:the averagemilkquotawas462,100kgfor59.5lactatingcows
infarmswithcubicles,tobecomparedtothe308,800kg ofmilkquotaand theaveragenumber of43.1lactating cowsinfarmswithoutcubicles.TheNUMBalsoinfluenced MAMthroughitseffectonthepresenceofhyperkeratosis. Theaveragepercentageofcowswithhyperkeratosiswas higherinlargerfarms:infarmswithmorethan50 lactat-ingcows,21.7%ofcowspresentedlesionsofhyperkeratosis for17.8%infarmswithlessthan50lactatingcows.Haskell
etal.(2009)arguedalsothattherelationshipbetweenherd
sizeandSCCmaybeindirect.
SomelatentvariableshadnoeffectonMAM.For exam-ple,thelatentvariabledescribingthetime necessaryto preparetheudder(MLK),hadnoeffectonMAMbutKiiman
etal.(2005)observedhighbulktankSCCwhenthetotal
udderpreparationwasshort(averageof30s).Thepractice ofexaminingforemilktofacilitateearlydetectionof clin-icalmastitisobservedin78.2%ofthefarmswasalsonot associatedwithMAM.Interestingly,Jayaraoetal.(2004)
observedthatbulktankSCCwashigherinherdsthat prac-ticefore-strippingbeforemilkingthaninherdsthatdonot.
5. Conclusions
Thisstudydescribedastructuralequationmodelwith latentvariablestounderstandtherelativeinfluenceofrisk factorsonalatentmeasureofthestateofmastitisinherds fromaparticularregionofBelgium.Variablesassociated directlywiththelatentmeasureofherdmastitiswerethe additionofureaintherations;thepracticesofmachine stripping,ofteatdisinfectionbeforeandaftermilking;the presenceofcowswithhyperkeratoticteats,offree-stallon cubiclestohouselactatingcowsandofdirtylinersbefore milking;thetreatmentofsubclinicalcasesofmastitis;and anlatentmeasureoftheageoftheherd.Teatdisinfection aftermilkinginfluencedalsothelatentmeasureofherd mastitisthroughitsassociationwiththetreatmentof sub-clinicalcasesofmastitis.
Acknowledgments
ThisstudywassupportedbyEADGENE(European Ani-malDiseaseGenomicsNetworkofExcellenceforAnimal HealthandFoodSafety).Theauthorswishedalsotothank theOSAMteamthatcollectandstorethedata.
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