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American Mineralogist, Volume 64, pages I I l5-I121, 1979 Trends in ternary petrologic yariation diagrams-fact or fantasy? Josu C. Burlpn Department of Geology, University of Houston Houston, Texas 77004 Abstract For more than 75 yearspetrologists(among others)have made use of triangular variation diagramsto illustrate comfositional variability among membersof a predefinedigneousrock suiG and to draw geneticinformation from the spatial positioning of the points on the diagram. when ternary percentagesare formed, the summaryunivariate and bivariate statistics of the ternary percentageswill usually differ from their counterpartsin the parent data array. Such changesare due entirely to the eflectsofpercentageformation. For example,reversals in the rank order of variancesoften occur, with the result that the variable with the smallest variancein the initial array may have the largestvariancein the ternary array. Such changes may be understoodby examining the row sum variable (the sum of the valuesof the initial variablesselectedto createthe ternary array) and the correlationbetweenthe row sum variable and eachof the initial variables(the part-whole correlation).The correlationcoefficients betweenthe three ternary variablesare likely to differ considerablyfrom their initial values. The net effect is that any observedternary trends must be consideredto result from a complicated set of interactionsincluding: (l) the sampling strategyused to assemblethe initial data set;(2) the summarystatisticsin the initial data setwhich themselvesare subjectto modi-ficationby percentageformation; (3) the part-whole correlationsin the initial data seq (4) restrictionson the variancesofa closedternary anay; (5) modificationsofall univariate and bivariate statisticsaccompanyingternary percentageformation; (6) petrogeneticcontrols' Unlessa rational meansof separatingtheseeffectsfrom eachother can be found it would appear to be unprofitableto attempt to basegeneticstatementson ternary variations. which are readily observed when diagrams are used to representnumerical figures.Moreover, visual memory is sufficientlydevelopedin most persons to enable them to carry in mind simple geometrical forms, where it does not permit them to recollect manifold assemblagesof oft-repeated numbers. Mental impressionsof simple diagrams, therefore,are more definite and lasting and enable the student to store up a much greateramount of quantitative data than he could otherwise acquire." "It is frequently supposedthat curves drawn in ternary diagrams reveal fundamental relations between the variables.. ." (Chayes, 1961, p. 160) Introduction For more than 100yearspetrologistshave debated how to most effectivelyportray the chemistry of igneousrocks for classificationpurposesand for revealing underlying petrogeneticprocesses.Particularly revealing are lddings' comments (1903, p. 9) concerning the necessityfor reliance on graphical de- Most of Iddings' comments were directed towards vices: classificationproblems and strategies,but it seems numerobvious that his basic philosophy has been adopted of the amounts in variations "The intricate comby many whose primary coneern lies in elucidating of chemical or components ous mineral petrogeneticrelations. their to comprehend most attempts ponents,bafle It is hard to disagreewith Iddings' desire to unby or contemplation simple by interrelationships a complicated situation, but it is inexcomplicate may be which they in numbers study of the the user to ascertainwhether the maupon cumbent overlooked are relations and facts pressed.Many 9/09to-l t I 5$02.00 w3 o04x/7 ll15 BUTLER: TERNARY PETROLOGIC VARIATION DIAGRAMS nipulations required to prepare the graphical device have in any way modified the relationsamongthe selected variables.For example,Chayes(1971,p. 7l) noted that many of the data manipulation schemes commonly resorted to by petrologistsresult in distortion of such magnitude that many of the trends are more a measureof numerical consequencethan petrogeneticreality. Of particular interest (to the author and most petrologistsit would seem)are the ternary variation diagrams such as CaO-NarO-KrO (CNK) and total iron-MgO-(Na,O + K,O) (FMA). Iddings (1903) credits Becke(1897)with being the first to represent the compositionsof igneous rocks by recalculating Ca, Na, and K to lOOTo and plotting this information on an equilateraltriangle in which the zeropoint was at the center of the diagram. Reid (1902)appearsto have been the first petrologistto use the modern triangular diagram in which eachside of the triangle is divided into 100parts. Since 1902 many petrologic presentationshave made use'of either the CNK or the FMA (or both) typesof variation diagrams,and it appearsthat many of the users have inferred that the principal factor governingthe configurationofthe observedtrends is relatedto someprocessof crystalfractionation. Wright (1974,p. 236-237)argued against the use of FMA diagrams for deducing petrogeneticinformation for the following reasons: Barker (1978) agreed in principle with Wright's objectionsto the continueduseof the FMA diagrams but arguedthat "the significanceof trends on alkaliiron-magnesium diagramscan be better understood by examining the relations betweencompositionsof rocks and their constituentminerals when projected on the AFM plane." An expectedchangein all of the univariate statistics of the selectedvariablesand in any of the pairwise measuresof associationis the most insidious consequenceof forming ternary percentages.Not only do the observedtrendslead to non-quantitative expressionsof mineralogical control (Wright, 1974), but it is conceivablethat an attempt to extract information of a qualitative nature (Barker, 1978)will fail to isolatemineralogical/fractionationeffectsfrom the numerical consequencesof ternary percentageformation. The purposeof this note is to review the effectsof percentageformation on the properties of ternary variablesand to assessthe probability of determining tlae underlying causesof the trends commonly observedin FMA and CNK variation diagrams. Preparation of the ternary diagram and the partwholecorrelation The general topic of the effectsof percentageformation on the properties of the included variables has been reviewed admirably by Chayes (1971, p. 36a! and will be referredto only with respectto (l) For most igneousrock seriesthe amountsof the the ternary case.When we decide which variables oxides combined to form the FMA diagrams (single or in some combination) will be used to decompriseconsiderablylessthan 50Vo(by weight) fine the ternary subset,the original values (which of the samples. constitute the initial data set) are recalculated to (2) Trends which appear to be significant can be l00%o (in order to keep the notation as simple as poscreatedby mixing togethersampleswhich obvisible, unprimed letterswill be usedto refer to the iniously have no geneticrelationships. tial variables primed letters to the ternary perand (3) Normalization to l00Voof sums that are not the centages): samedistorts the plots with the result that trend orientationsdo not quantitatively expressspecific Ai: 100(AtlTJ (l) mineral controls. T, is the sum of the valuesof A, B, and C in the ith Similar statementscan be madeconcerningthe CNK row of the data matrix: or any other conceivableternary variation diagram. Ti:Ai+Bi+Ci (la) If one wishesto define total variability as the sum of the variances of the measured oxide components It is useful to focus attention on the summary statis(Chayes, 1964), the FMA and CNK components tics of the three initial variablesand the row sum (T) generally account for considerablyless than 25Voof in order to understand and appreciatethe effect of the total variability of the rock suite being investi- percentageformation in controlling ternary trends. gated (Butler, 1975),and one gets the feeling that a The importance of the row sum statistic cannot be considerablequantity of potentially useful informa- overemphasized,although it is unlikely that the intion is being ignored. vestigatorwould bother to computeits summary sta- BUTLER: TERNARY PETROLOGIC VARIATION DIAGRAMS tisticsor to treat it as anyhing other than a necessary stepin the transformationprocedure. If the initial variables (A, B, and C) are uncorrelated (in which case the Pearsonproduct moment correlation coefficient-r---equals zero),there will be a positive correlation betweenany one of the initial variables and T (this type of correlation will be referred to as the part-whole correlation as, for example, A is part of T---+quation la): ro-. : so/st (So * sgras + s.ro.)/st MEAN srD (2a) From equation (2a) it is clear that the part-whole correlation may be positive or negativeif the initial variablesare correlated,and that the sign ofthe partwhole correlation is controlled by the signsand magnitudes of the correlationsbetween the initial variables.Any data set in which the sum of the valuesof the variables is a constant for all of the samplesis consideredto be a closeddata set. The standarddeviation ofthe row sum variable (s') in a set of closed data is equal to zero, and the part-whole correlation (equations 2 and 2a) is undefined. Wright's (1974) third objection to the use of the FMA variation diagramsstemsfrom the fact that the initial valuesof F, M. and A do not constitutea closeddata setby themselves. I have examinedthe propertiesof many ternary arrays from a variety of published setsof chemical information (Butler, 1975),and the set of I 14 chemical analysesof igneous rocks from the Big Bend National Park area of west Texas(Maxwell et al.' 1967) has been selectedto illustrate the effectsof ternary percentageformation on the properties of the individual variables and to analyzethe trends that are frequently observedin the CNK and FMA types of variation diagrams.Summary statisticsfor the CNK and FMA subsetsare given in Tables I and 2 respectively. Effect of percentageformation on the mean of ternary variables A seriesof approximationscan be derived which allow estimating the properties of ternary variables DEV. cao 4.42 Na2o' 17:18 24.49 3.78 9'67 0 95 0.77 0.86 0-26 o'21 9'63% O.O9% 26'26"1 61.767. l-47% % VARIANCI Na2O xzol 4'55 31.18 cao' 31.35 coE!. vAR. 0.58 o-37 SKEWNESS -0.32 \5'97 0-51 191tl-lw 12'64 L'63 2'2r 0'44 0'18 0 277" -0'2E -0 20 0'05 KZ9 3'68 CORREI,ATIONCOEI'I'ICIENI MATRIX K2o RolI StM *20' Na2o' Na2o -0'905 0 782 1.OoO 0.910 -o'925 -o'563 -0'973 1.000 -0.925 -0'564 -0'958 -0'888 0'817 cdo cao' cao' (2) where s is the standard deviation of the variable identified by the subscript.Similar equationscan be written for variables B and C by appropriately switching the subscripts.If the initial variables are correlated (r # 0.0) the part-whole correlation betweenA and T is given by: fnr: Table l. Summary statisticsfor ll4 west Texas analyses:CaONa"O-K"O cao -N- ,2 -o ' 1.OOO O 7OI O 813 O 752 -O 724 Na2O 1-000 0'438 0'629 -0'042 1 .000 0.932 -0 761 "2' Kzo l ooo -0'509 1 ooo Row sw AND TERMRY MEANS @MPARISON OF INITIAI. I'ACTOR* INltlAL MEAN VARIABTES TTRMRY MEAN PRXDICT'D EO (34) CaO'CaO 0.908 4.42 31.63 34 97 Na^O'-Na^O 1.012 4.55 37.18 35.97 3I.r8 29.07 l.o7l ? J.68 (1 - rArcAcT + ci) KrOi-K2O *-FAcrOR - COM?ARISONOT INITIAL I'ACTOR* VARIABLES AND TERMRY VARIANCESAND S(EIINESS INITIAL VARIANCE TERNARY VARIANCE I* cao'-cao 0.516 74.29 599.62 -0.52 Na20'-Ne20 K2O',-K2O 0.078 0.90 93.51 0.18 0.306 2.65 254.99 0.40 = R< ' o * * FACTO * "f, - 2.Ar"oar) I- = (CT-rATCA) from the properties of the initial variables (Chayes, 1971; Butler, 1978). Chayes' first-order approximation for the mean of a percentage is given by: F: 100(F/D (3) That is, the mean of a ternary variable is approximated by 100times the ratio of the mean of the initial variable to the mean of the row sum variable (T). The ratio of the ternary mean to the initial mean (R.) is givenby: R.: F/e: loo(-AlD/T: roo/T (3a) Obviously, the ratio R. will be the same for all three variables. From Tables I and 2, however, it is clear that the ratio of the means is not constant for all three variables. A second-order approximation for the mean of ternary variables (Butler, 1978) is given by: F : 100(tD(l - ro,C^C,+ Ci) (3b) where C is the coefficient of variation (the ratio of the ll18 BUTLER: TERNARY PETROLOGIC VARIATI1N DIAGRAMS Table 2. Summary statistics for I 14 west Texas analyses: total iron_MgO_(Na2o + K2O) Meo' MgO ALruIII HEAN 11.00 2.39 51.81 ATKAI,I IRoN' lRON 8.23 37.L9 6.93 17.54 ROW S1IM STD. DEV. 12.34 3.t0 21.94 2.35 12,46 3.43 4.35 COEI. VAR. 1.I2 1.23 0.42 0.28 0.34 0.50 o.25 7. VARIANCE 14.247" r.r5% 57.67% 1.7r -0. 17 SKEWNESS 1.32 0.667" ra.60% -0.32 _0.30 1.4r7. 0.11 MCO' 1.000 Mgo MgO ALKALI, ALKALI IRON IRON 0.992 _0.894 _0.829 0.566 o.760 1 . O O O- O 8 4 5 - 0 . 7 9 9 0 . 5 0 5 0 . 7 1 8 ArKAtl' 0.860 0.849 -0.913 1.o00 -o.645_0.723 _O 602 r.ooo 0.940 IRON 1.000 ROWSW FAcoR* INITIAL mN AND TERNARY MEANS TERNARY MEAN PR.EDTCTED EQ (3a) Msor-Mso 0.788 2.39 1t.OO 13.61 ALKALI'-ALKALI 1.104 a.23 51.81 46.88 rRoN,-rRON 0.950 6.93 37.19 39.50 * IAcToR= t r- .o.o", * .f) COMPARISONSOF INITIAL FACTOR* uso'-Meo INITIAL VARIANCE AND TERNARYVARIANCESAND SreWNESS TERNARY VA.R.IANCE ]-** 1.201 9.6r 152.27 _0.85 Ar,KALr'-ALKALT 0.227 5.49 48t.44 0.42 11.78 r55 25 _0.20 rRoNf-rRON 0.75: o.9ll 1.00tJ CO},IPARISONOF INITIAI 0.083 * F A C T o R= < " 1 , * I - 2ro,coc,) (4) ROII SW 1.OOO 0.832 _0.886-0.962 rRoN, sl. : 10"(-AlD1c1+ c|- The ratio of the ternary variancesof variablesA and B is given by: CORRSI"A.TION COEFI,ICIEIfI MATRIX ugo' mation and that such changes are not easily explained. The variance of a ternary variable can be approximatedfrom the propertiesof the initial variablesby (Chayes,l97l; Butler, 1978): 2.Ar"A.r) *1=(CT-TATCA) standard deviation to the mean) of the variable iden_ tified by the subscript and ro, is the part-whole correlation (equations 2 and 2a). From equation 3b it is clear that if ro, is negative, the ternary mean will exceed that predicted by equation 3. Sirnilarly, if ro, is positive and greater than the rutio C,/Co, the ternary mean will be less than that predicted by equation 3. For example, the mean of total alkalis (Table 2) is considerably increased (51.81) compared with the value predicted by equation 3 (46.89) and those of MgO and total iron are correspondingly decreased. From Table 2 the mean of CaO in the parent set @.42) is considerably greater than that of K,O (3.69), yet the ternary mean of CaO (31.63) is only slighrly larger than that of K,O (31.18). Although not illustrated in Tables I or 2, a reversal in the rank order of the means can occur as the result of percentage formatron. Effect of percentage formation of the variances of ternary variables Chayes (1962) noted that the variances of ternary variables often change markedly following transfor- s2^,/s?8,: IG; XC; )(C^,+ C,, - 2ro"CoC,)l /lG; XC; XC",+ C,, - 2r",C"C,)l (4a,1 which was written in a form which emphasizesthe relationshipbetweenthe initial variancesand the ternary variances.The behavior of MgO and total alkalis (Table 2) illustratesa situation of frequent occurrence.The variable with the smallestvariance in the initial data set (total alkalis) has the largestvariance in the ternary subset.Although there is a large number of variablesin equation 4a, severalgeneralizations can be made concerning reversalsin variancerank order: (l) Reversalsin rank order of variance are favored when the variable with the largestinitial variance has the largest initial coefficient of variation (other quantitiesbeing equal). (2) Reversalsin rank order of variance are favored when the variable with the largestinitial variance has a positive part-whole correlation and the variable with the smallestinitial variance has a negativepart-whole correlation (other quantities beingequal). In all the FMA diagrams examined by the author (identified in Butler, 1975),the behaviorexhibited by the initial and ternary variablesis very similar. F, M, and A accountfor a very small percentageof the total initial variance (usually lessthan l}Vo), and total alkalis have the smallestvariance in the initial set and the largestin the ternary subset. Even when reversalsin rank order of the variances do not occur, changesin the ratio ofthe variancesalmost always occur when ternary percentagesare formed (Tables I and 2).It seemsintuitively reasonable to expectthat the trend and scatterappearingon any form ofternary variation diagram in part reflect the variances of the variables. Given the fact that major reversalsof variance can occur simply as the result of ternary percentageformation, it should be just as reasonableto expectthat at least part of any trend may be artificial. BUTLER: TERNARY PETROLOGIC VARIATION DIAGMMS ll19 Effect of ternary percentage formation on the skewness of ternary variables The skewness of a variable is a measure of the asymmetry of its distribution. Pearson (1926) noted that a ratio formed from two symmetrically distributed variables (zero skewness)will have an asymmetrical distribution (non-zero skewness). The sign of the skewness of such a ratio (for example, A/T) will be given by the sign of L (Merrill, 1928): Lo, : C, - rorCo (5) As the initial variables in a set of chemical analyses commonly have non-zero values of skewness, L", (5) does not give the sign of the skewness but does indicate the direction of change of skewness following ternary percentage formation. For example, MgO (Table 2) has a skewnessof l.7l in the initial data set, and the computed L."o. of -0.85 indicates that percentage formation should and does decrease the skewness to 1.32. In general, it does not make sense to worry about a genetic interpretation of skewness of a percentage, as its sign and magnitude may be numerical rather than petrologic in origin (Butler, 1978). Effects of percentage formation on the total variance of a closed array and on the correlation between a pair of variables Chayes (1961, 1962) showed that no closed standard deviation can be as large as the sum ofthe standard deviations of the remainder of the variables. The situation where one standard deviation equals the sum of the other two (in the case of ternary percentages) can occur only when that variable is perfectly negatively correlated with the other variables and the other variables are perfectly positively correlated with each other: Se.: ss.+ s., if, and onlY if, rls: r|c: -1.0 andr!": t r2 u Na20 Fig. l. CaO-Na2O-K2O data set. variation diagram for the west Texas near the CaO apex and extends to the NarO-KrO limiting binary. Qualitatively it appears that the linear trend expressed in Figure I evolves into a simple curvilinear trend as the quantity (s". * s..) departs from so and rns, rnc, and r". approach 0.0. The FMA variation diagram for the west Texas data set, given in Figure 2, appears to be typical of curvilinear ternary plots. The trend is initiated near the apex where the variable with the largest standard deviation is plotted (total alkalis for Fig. 2), arrd the inflection point is nearest the apex where the remaining variable with the largest mean is plotted (total iron). One normally considers the correlation coefrcient (6) 1.9 A plot of the ternary variables which obey these relations will define a straight line in an equilateral triangle. The line heads away from the apex of the triangle at which the variable with the largest standard deviation is plotted. As the quantity (s", * s.,) begins to exceed so,, the straight line is replaced by a linear trend and the three correlations depart from an absolute value of 1.0. The CNK diagram for the west Texas data set, given in Figure l, is typical of other CNK plots examined by the author. The trend begins AtK ATIS Fig. 2. Total iron-MgO-Na2o west Texas data set. T()TAL IR()N + K2O variation diagram for the I 120 BUTLER: TERNARY PETROLOGIC VARIATION DIAGRAMS to be a measure of the strength of the linear pair-wise association between a pair of variables. However, Chayes (197l) showed that the correlation between a pair ofternary variables can be expressed as a function ofthe variances ofthe three ternary variables: r",c, : [s1,,- (sr",+ sr.,)]/2sis! (7) expected as a function of the variances of the variables which are a function of: (l) the sampling strategy used to construct the data array and (2) the partwhole correlation. Miyashiro (1975), in fact, argued that a complete gradation exists between the tholeiitic and calc-alkaline suites. Barker (1978) artributed the increased scatter of the typical calc-alkaline trends in an FMA variation diagram to a more pronounced fractionation of plagioclase. However, as evidenced by the previous discussion, ternary curvilinear relations are characterized by two correlations with relatively large negative values and one correlation that is usually positive but may be close to zero. Thus, one should expect greater scatter with a curvilinear trend than with a linsil trend, regardless of whether plagioclase is precipitating from or dissolving into a magma; unless, of course, one could relate plagioclase behavior to the part-whole correlation in the initial data set. where similar expressions can be given for r^,", and ro.", by appropriately switching subscripts. From equation 7 it is clear that ternary variables pose a difficult problem in interpretation. The correlation between a pair of ternary variables (for example, B, and C') is positive if, and only if, the sum of the variances of B' and C' is less than the variance of ternary variable A'. If all three initial variables are positively correlated, only one pair of the ternary variables will be positively correlated and, commonly, all three pairs will be negatively correlated. In the CNK and FMA diagrams examined there are no reversals in the sign of the correlation coefficients, but there certainly is a Extension of the preceeding arguments to the initial change in their magnitudes (see Tables I and 2). For data set example, the correlation coefficient between initial values of MgO and total iron (Table 2) is 0.760 and Chayes (1971, p. 4445) has argued that a chemthat between the two ternary variables is 0.566. If the ical analysis is closed by observation. Errors of omisother two correlations (between MgO and total alsion and/or commission account for the fact that a kalis, and between total iron and total alkalis) were good analysis will comnonly total between 98.5 and to remain constant and if the correlation between 101.5.The point is, one must recognize that the uniMgO and total iron were to approach 1.0, the trend variate and bivariate statistical properties ofthe parwould approach linear behavior, whereas if the value ent data set contain some contribution from the clowere to approach 0.0 the trend would become curvisure effect. linear with an even more pronounced curvature Wright's (1974) objection concerning normal(compared to Fig. 2). ization to l00%o of sums that are not constant has In summarizing the difficulties inherent in working been discussed previously. In the same discussion with ternary variables, Chayes (1961, p. 16l) stated Wright suggests that petrologic relations can be best "many of the alleged ternary trends are probably discerned by using a bivariate plot of MgO vs. all best regarded as complicated and camouflaged state- other major oxides, rather than by using SiO, (which ments of variance relations largely controlled by the leads to the familiar Harker diagram) for the mafic criteria set up in the sampling plan." Recalling that and ultramafic suites. All binary variation diagrams ternary percentage formation can result in major (including Harker diagrams and Wright's MgO varichanges in variance and in the rank order of the ation diagrams), while reasonable on petrologic three variances, Chayes' reference to ,.camouflaged grounds, fail to consider that an unknown portion of statements of variance relations" must be taken seri- the observed correlation and scatter is the result of ously. Perhaps, however, it would be more appropripercentage formation. At this time it does not appear ate to say that the ternary trends are best thought of possible to satisfactorily separate the effects of peras reflections of the part-whole correlations present centage formation from fractionation, assimilation, in the parent data set. or whatever petrologic model the investigator may Irvine and Baragar (lgil) argued that tholeiitic have in mind. (simple linear) and calc-alkaline (curvilinear) suites Wright and Hamilton (1978) suggestedusing MgO could be easily distinguished by their trends on FMA variation diagrams to define chemical types of igvariation diagrams. As noted above, however, a graneous rocks. Samples from an igneous unit that is dation between these two end-member trends is to be stratigraphically restricted are plotted on such a vari- BUTLER: TERNARY PETROLOGIC VARIATION DIAGRAMS ation diagram and used to define a polygonal field which may aid in characterizingthe chemicaltype of unit and aid in identifying unknown samples.The spread of data points on such a binary diagram reflects the variancesof the plotted variables and the correlation betweenthem. As both the variance and correlation are likely to have been modified by percentageformation, the shapeof the defining polygon may have a componentdue to the closureeffect. tt2l unprofitable to attempt to basegeneticstatementson ternary variationsby themselves. Acknowledgments Earlier drafts were reviewed by Max F. Carman and Dan Barker. Felix Chayes gave a detailed critical review ofthe manuscript which is greatly appreciated. Judy Butler assisted with the drafting. The Geology Foundation of the University of Houston supported this work. References Summaryand conclusions The preceding discussion shows that when one forms percentagesthe summaryunivariate and bivariate statisticschange.This effectmay be so drastic as to changethe rank order ofthe means,variances,and correlation coefficientsso that, for example,the variable with the smallestvariancein the initial data set has the largestvariance in the ternary data set. This combination of changes in means, variances, and correlationsmanifestsitself in the nature of the distribution of the sample points in an equilateral triangle.Simple linear and curvilinear trendsare gradational as revealedby the following relations: l. straight line: fec : fen : -1.0 and r". : +1.0 2. linear trend: 3. curvilinear: ro. and rAB are large negative; r". is large positive rr.. and rAB are intermediate to large negative; r". is intermediate to small positive Therefore, the observedternary trend must be considered to result from a complicated set of interactions including: (l) the sampling strategyused to assemblethe initial data set; (2) the summary statistics in the initial data set. which themselvesare subject to modification by percentageformation effects; (3) the part-whole correlationsin the initial data set; (4) restrictionson the variancesofa closedsubset;(5) modifications of all univariate and bivariate summary statisticsaccompanyingternary percentageformation; (6) petrogeneticcontrols. Unless a rational meansof separatingtheseeffects from each other can be found, it would appearto be Barker, D. S. (1978) Magmatic trends on alkali-iron-magnesium diagrams. Am. Mineral., 63, 531-534. Becke, F. (1897) Gesteine der Columbretes. Tschermak's MineralPetrogr. Milt., I 6, 308-336. Butler, J. C. (1975) Occurrence of negative open variances in ternary systems.Math. Geo|.,7,3145. -----{ l9?8) The effects of closure on the moments of a distribution. Math. Geol., in press. Chayes, F. (1961) Numerical petrology. Carnegie Inst. Wash. Year Book, 60, 158- 165. ---11962) Numerical correlation and petrographic variation. "L Geol.,70,440_452. -----11964) Variance-covariance relations in some published Harker diagrams of volcanic suites. J. Petrol., 5, 219-237 . -<1971) Ratio Correlatioz. University of Chicago Press, Chicago, Illinois. Iddings, J. P. (1903) Chemical composition of igneous rocks. U.,S' Geol. Surv. Prof. Pap. 18. Irvine, T. N. and W. R. A. Baragar (1971) A guide to the chemical classification of common volcanic rocks. Can' J. Earth Sci., 8, 52t-548. Maxwell, R. A., J. T. Lonsdale, R. T. Hazzard and J. A. Wilson (1967) Geology of the Big Bend National Park, Brewster County, Texas. Univ. Texas Publ.67lI. Merril, A. S. (1928) Frequency distribution of an index when both components follow a normallaw. Biometrika, XXII,53-65. Miyashiro, A. (1975) Volcanic rock series and tectonic setting' Ann. Rev.Earth Planet. Sci.,3,251-269. Pearson, K. (1926) On the constants ofindex-distributions as deduced from the like constants for the components of the ratio with special reference to the opsonic index. Biometrika, XX, 43t-41. Ried, J. A. (1902) The igneous rocks near Pajaro. Univ. Cald. Bull. Dept. Geol., 3, 173-190. Wright, T. L. (1974) Presentation and interpretation of chemical data for igneous rocks. Contrib. Mineral. Petrol., 48,223-248. -snd M. S. Hamilton (1978) A computer-assisted graphical method for identification and correlation of igneous rock chemisties. Geologlt, 6, 16-20. Manuscripl received, November 13, 1978; acceptedfor publication, April 5, 1979.