ICES STATUTORY MEETING 1993 C.M. 1993/d: 11 Sess.P . "' HOW TO REDUCE THE IMPACT OF MODEL UNCERTAINTY ON ASSESSMENTS AND ADVICE by lake Rice Department of Fisheries & Oceans Pacific Biologica1 Station Nanaimo, B.C. Canada V9R 5K6 ABSTRACT Assessments and projections can have uncertainty because data are noisy or unrepresentative, and because model formulations do not capture the biological processes correctly. When scientists quantify risk, they lose none of the uncertainty due to data sources. Moreover, they may add further model uncertainty because they must specify the error structure of the models, as weIl as the biological processes. . Non-parametric density estimation methods estimate the probability density function (pdt) of attributes from data, without specifying a particular functional relationship or error distribution. Non-parametric density estimation, methods can forecast the pdf of features like recruitment or weight-at-age from biological and/or physica1 influences. They can also capture environmental vanability in tuning indices without having to specify the relationship between the index arid the environmental factor (say, survey estimates and water temperatures). The quantitative results can be displayed as probability distributions or ogives. When models ,are well motivated, or model parameters are of direct interest, model-based methods should be used to quantify uncertainty. When there are~reasons to question any particular model formulation, non-parametric methods are useful for representing the true uncertainty in the advice and the range possible outcomes of management actions. From my , experiences using distributions and ogives to present iesults to managers, I will draw some generalizations about the effectiveness of each type of display, and how each can influence decisions. .' C.M. 1993/D: 11 ICES STATUTORY MEETING 1993 •,, i Sess~P , Page 2 j .' I INTRODUCTION i . , , ,',. , " '." , .1 , , ' ',,, .,,", . ,." ., Both the models we use to represent fish populations and fisheries and the data we use to parameü~rize the models determirie thequantltiltive advice we give on the status arid management of fish stockS. Both the models arid the daci are impenect. The imperfections are major comporierits of thc unceriairity in adviee arid the nsk iri management options. I Data can be made less imperfed through impr6ved 'suivey cind sampÜng designs,: through collection of more data; arid through better tools ror making measurements. Nonetheless data will riever be perfect. Wheri scientists estlmate risk or 'uncertainty, the error or variarice in the daci will coritribute to the estimates. I • , I The models which use the data eire inlerided to represerit actuaI biologicaI processes. At best the models simplify and may misspecify the.i-eaI pröcesses.!Moreover, the quarititative models must not only specify the furictional relationship between entities (say, stock arid recruitment), but the models must speeify, the form of the vanability around thai furietion'aI relationship (the error term). Models can be improved throiJgh research ori!biological and fisherit~s proeesses; and througn approaches to inodel selectiori which render paor models implausible iri compärlson to good models. I . ,I The first strategy, is limited beeause good flsheries research takes time. The secorid 'strategy is limited by. the ,quality arid quantity of datei avmlable to~ diserimiriate, among alternative models. Everi good data are often incorichisive or contradidorY (e.g. Walters 1985; Richaids 1991)~ Theiefore, everi many widely used models have been chosen for mathematical convenience rather thari for any strorig theoretical or empirical justification (e.g. Ricker 1954). Now, the computing power available routinely to most fisheries scientists has deereased our rieed for t h e " mathematical "convenieriee" of simple functioriaI relationships in fisheries models. • cW~ters Estirriating model parameters from pooi data ean mcikel everi good models go bad arid Ludwig 1981, Schriute & Hilborn in press). Conversely, why put good data irito a model which misspecifies functional relationships or error distributions?, We would be adding additional inäccuracyto the level ofüriceI'tainty aIready present in thc data themselves.' lri those cases we can apply quantitative tools whieh use the data directly; ~ithout iriterposing beiweeri the data and tne advice functional relatioriships or error terms in whieh we have little faith. Nonparametric density estimatiöri methöds eire one class of such tools '(Silverman 1986). . • • . . ' I I I ., l . ANALYTICAL METHODS tI , l " I , . Evaris and Riee (1988) deseribe one simple nonparametric density estimation in detäil; a keinel estimator based on tne Caucny distribution. The' kenlel cari use the same data as' functi6rilli. models; say pairs of historie ssbs arid reeruitmerits. The; kernel estimates the probability density 1 , I ! i i I, .' "- ICES STATUTORY MEETING 1993 C.M~ 1993/D: 11 Sess.P Page 3 ," function (pdf) for recruitmerit given a new ssb (forecast or estimated) by weighting each historie recruitment by the similanty of the historie ssb which produced it to the new ssb. The weighting furictlori is:' • Dis a. tuning parameter estimated through crossvalidatlon (Bowman, et al. 1984). The xj'sare the differerices between the "riew" ssb and eäch of the i historie ssbs. The Wj'S are sCaled to sum to 1.0. The scaledweights are, themselves, the estimated pdf. NatufaIly,any pair of variables be sut>stltuted for stock and recruitmerit, and users can smooth the estimated pdf further, if desirect. can Evans arid Rice (1988) report results of simulations which show tilat the kernel estimator performed as well or better (smaller average error, much better worst case performance) than traditiorial parametric approaches to stock - recruitment forecasting, except under ideal conditions. The "ideä1" conditions were that the tnie functional form of the stock - recruit relationship wa.s specified correct1y, AND the error tenn waS specified correct1Y"ANti the noise (contribution of the error term to the. simulated data) was small compared ,to ,the signal [coritrlbütion of the furictiorial relation to the simulated data]. Riceand Evans(1988) and Rice (1993) illustcite applications of the Cauchy kernel to developing advice on rebuildirig fish stOCks and on fish - habitat iriteractions. APPLICATIONS TO RISK AND UNCERTAINTY • PROBLEM 1: Seiecting a rebuilding strategy. To forecast the effects of a management strategy, flsheries sdentists often must forecast exp~cted recruitrrient levels. For example, in 1977 Canada adopted a management strategy to rehuild the eod stock in NAFO Division 2J3KL. Decision makers needed projections of the trajectory the stock would take under different F's. Although concems about natural variation in reci"uitment were prominent in the ICNAF advice, there were no estimates of risk or uncertainty associated with the rebuilding forecasts. The stock and reci"uit data available at that time did not allow identificiltion of an appropriate stock reCruit function; because there was inadequäte information on, the cUrVature and desceriding limt> of the function, if either existed (Fig 1). Therefore; ICNAF ,assumed annual reCruitinerit would be the average of cohort estimates from 1962-1972 (ICNAF 1977). Rice and Evans (1988) used the kernel esti'mator to investlgate six questions about rebuÜding cod stock. Their answers included estimates of the range of outcomes possible given the data which were available in 1977. Suppose the explicit objective had been to achieve an SSB of 1.0 million metric torines (mmt) ,within 10 years., If recruitment are chosen without consi~eration of SSB (Le. if the kernel parameter D is riüide large rdative to the range of historiCal SSB's), r C.M~-1993/D: 1 ICES STATUTORY MEETING 1993 Sess;P' Page 4 i j J I the rlsk of faiÜng to achieve thai objective witb F=0.'16 is negligible (Fig 2a). If the kemei parameter is turied, the pdf of recruitment does vary with SSB arid the probability of failirig to achieve theit objectlve is 0030 (Fig 2a). Moreover, the approach allowed estimation of the full pdf of future SSB for different. values of F, so the probability of the stock achieving vanous targets \inder different management regimes could beevaluatoo (Fig 2b).. Interesting, ,when the work was done in 1986 the kernel algorithm estimat~ the median value for actual average fishingmortality bet'N.een 1977 arid 1984 to be 0.37.,This valuewas substintially higher than VPA estimatesat ttiat time, but fairly elose to currerit VPA estimates F in those Years.. Not only did the data-bcisoo method provide estimates of uncertainty directly; it also estimated the central moment weIl, compared to model-based methods; cf , _ " . i I " PROBLEM 2: Age Composition of PaCific Hake Catch ; , .. , : ,. • , , Camida and the US both fish the migratory stock of Pacific Hake (Merluccius produclUs). In a "typica1 year" the stock spawns in FebruarY off Southern California arid northerri Mexico, then migrates noi-th~ ·older fish migrate further, so the :Cariadian harvest, taken from. June to September, has ari older age' composition than the US harvest., In discussions concerning allocation of catch between the couniries, it has beeri argued that tonne for the tonne the Caileidicin fishery places the stock at higher risk, beeause it has a greater impact on spawriing biomass, arid therefore on future recruitment. I' '. I " .' ., ., ..,,,. I,,,, '.' • '' Hake year-elasses vary greatly. The mfluence of SSB on recruitment IS weal(; The data do not h~nd themselves to parametric analyses; again neither ttie pcilk of the dome nor the shape of the limbs can be determined with confidence (Swartzman; 'et al. 1983; Fig 3). We inc0rP0rated a Cauchy kernet estimator of recruitment from SSB into eilsimulation model of the hake population and fishery. We used the model to explore the effects of altering the eige composition of the combiried Canada - US harvest on future recruitment; future SSB's, cind future yields. Scenarios riuiged from age compositions younger than the preserit 'UScatch to age composiiions oider ihen present Canadiari catch (Table 1; data from Dorn arid Methot 1992). I ' ' . . .'. '. . . I . " . The cyclic nature of hake reeruitment is present in results of all simulations (Fig 4a), as is the skewoo and bimodal pattern in the frequency of occurrerice of cohort sizes (Fig 4b); Some catch is foregone with the olderäge composition' (Fig 5a), but SSB is actually higher (Fig Sb), arid catches aie more stable (Table 2). i' - ' . . .. . I I '.' ....- Fig\ires 4 arid 5. are averages of 200 runs, and do not reflect uncertaintyarid risk. The hake stock is managed with a strategy. which reduces exploitatiori significantly, whenever the SSB falls below a critica1 level. , Probability of reäching the crÜicaI level is available direct1yfrom the simulations. Suppose we ideritify the criticallevel as 0.225 mrnt (the value used in 1992); With an oider age composition of catch. the critical level is hit less often than with a younger age corriposition. One can examine the unceItainty of any 'features presented as averages in earlier figtires. For example, catches and ssb's after 20 or ~O years are highly skewed far all age compositions (Fig 6a,b). • ,', ICES STATUTORY MEETING 1993 C.M~ 1993/D: 11 Sess.P Page 5 PROBLl~M 3: Hydroacoustic Index of CapeÜri Abundance Anriual hydroacoustic s~iveys of capelin abundance are conducted in the Northwest Atlantic. Oceanographic conditions influence eapelin ,distributiori and aggregation patterns (Carscadden et at. 1989). To use the survey results as either an absolute or relative index of abundarice iri anassessment without accounting for oceanographic influences would include unnecessary variance and uncertairity. However, there' is no. theoretica1 justification. for any specific functiorial relationship between temperaiure and abundance. Inspectlon of the data suggests the relatioriship may not be smooth and coritinuous (Fig 7). Exploratory regression analyses produced statistically. significani fits to. the dati (Fig 7). However, model estlrriates were consistently biased at temperatures above 2°C and below O°C. Because of the aggregation of capelin, there also would be major probleins specifying the error term in regression-based models.. If both the central moments and the uricertainty estimates.of a model are unreliable, it is unlikely to estimate the risk ofvarious harvesting options accurately. Relating hydroacoustic estimates ofbiomass to oottom temperature with the Cauchy-based kernei accounted for over half the vanance iri the hydroacoustic estirriates (Fig 8). The ogives of abundance at different temperatures correspond weIl with the patterns in the origirial data. For very cold water (-0.5°C) only low capeliri densities are likely. The pdf changes little until temperature reaches + 1.5°C. Over the next 2°C, the upper limb of the ogive changes substiritially, however the ogives remain nearly flat between 2 arid 70 units of capelin. This reflects the schooling nature of capelin. Everi in preferred temperatures one does not expect "average" aburidarice of capelin. It is the likelihood of encountering high abundance which is varyirig. an • From survey data and maps of bottoni temperatures, one can construct a grid of ogives for the area. Algorithrris then cari estimate abimdance indict~s through resampling from the ogives or using other strategies. , Repeatoo estimation will represerit a reatistic pdf of actual abundance. The pdf niay be quite skewed arid irregular, but can be used directly io estimate the unceItainties and risks of varlous management options. PROBLEM 4: Trawl Index of Shrimp Aoundance Shrimp stockS in British Cohimbia are surveyed with trawls (BoutiÜier 1992).. BathometrY gives significant spatial structure to. the shrimp populations. Physical oceanography also influences distribution and aburidance. No furictional relationships have been develoj}ed to accourii for the spatlal or temperature irifluences ori the trawl Samples~' The management strätegy for shnmp stOCks inCludes ädvising dosure of fisheries when biorilass estirilates fall below a criticatlevel set for individual groiJrids. A miJitidiinensionalextension of the kernel estimator was used to estimate the pdf of aburidance for a grid of simple points. When constIucting the pdf of aburidance äi a giveri C'gricl ti ) ICES STArirrORY MEETING . < e.M. 1993 . i ,"-. 1993/D: 11 Sess.P Page 6 . . position, irifluence of each sampie point was weighted bY. the siinihmty of each siuriple point to the "grid" point on three factofs: temperature, depth, arid isotropie (positional) space (Evans et aI. ms)~ CrossvaJ.idation was used to seleet Cauchy parameters simultaneously for all 3 features. Differences inthe ratios of the wi~th of the tuning window to the range of observations for each feature provided the differential weighting of each feature when estimating the pdf of abimdance (fable 3 ) . · . I . . \. , . . ..' , . I . I '. ':' . The ogive mapping procedure produced a pdf of abundance ateach point on ci spatial gnd over the areä. The anllual abundarice estimate; arid the uncerciinty' around that,estimate, were estimatecI through repeated samplirig from the gnd of. pdfs.. That overaIl pdf of aburidance provides a direct estim.tte of the probability that the stock lies lJelow the criticil1level. The pdfs are estimaterl without having to develop ovenui, parameti"ic relatioriships between shrimp abulldance arid temperature, nor detmled parametrle models of the spatial distribution of shrimp Oll each fishing ground. Pacimetiie versions of such models, and paftlcularly parameterized error terms and uncertainties of such models, ha.ve riot been produced. • , 1 J ,, \ Corisider problems like estimating. how nsk to the stö~k vanes with age composition of hake catches~ It may tie possible to develöp model-based representations of recruitment dyriamics and use these to estirriate risk. It would require finding normalizing transforinations, obtmnirig stable estImates of error diStributions, and many other steps.. The best models could only be approximate ones. Moreover, given the data, it would be extiemely difficult to rejeet many different representations of the functional relationships'and eITOrS of stock and recruitment, yet cit least some representations would have to be wrang. I " ..\ ; .. " . , . ' ~ ., . '. ,- ."" ., "'. . ·,-,·t - -, ' '> . _ , , I are A careful cidvisor would run' forecastS with all the rilodeis arid error stIlictures which plausible given the data (cf Richards 1991). As a result the range of possible outcomes would increase, compared to results ofany single model. i The data already cOIltain substantial uncertainly abotit the future dynamics of the stock. Proper use of model-based approaches cari only' add uncertairity, and scierice advisors would assign less certainty and greater risk to any management option. ' I . I We can use the data direct1y tri produce the necessary forecasts and unceriainty estimates.. These Can bei relateddirectly to the decisions managers inu~t ~ake. What additionaI pUrP0se is served by addition of weak1y suppoited models? 1 . j I 1 I· • ICES STATUTORY MEETING 1993 " <, , , C.M. 1993/D: 11· Sess.p Page 7 ' . , WHAT DO WE REALLY WANT TO KNOW ABOUT RISK? As we focus ori assessing risk arid l1ncertlinty in fisheries advice änd mariagement, many deeisioris depend more on the shape of the tails of ci distribution thari on its central moments. Mariagers inay wish to keep unpleasarit everits rare, or enhance irifrequent opportunities. , • As the capelin example show&!; model-based estimates can be especially pOOl' away. froin the average condition; Moreover, the mean condition may be unlikely. It can be arguect thatmore sophisticated models, atlowing. for aggregatect targets änd complex patterns of eITors, address concerns about entire distributions rather than just centriU moments. Again, one has only the data to guide the proper treatment of error. If the data often. are inadequate to discriminate among alternative functional relationships, is it likely they would be better ableto identify the proper error structure? Data-based methods areri't a eure-all, but they ean be helpful. PRESENTATION OF RESULTS In this paper I have usuatly presented results as curilUlative frequency distrltiutions (cfd) rnther thanas pdfs. Both contain the same information. Which manner of presentation conveys the key information more effectively? In my experlence, effectivenes~ depends on the nature of the message. PDF's are more familiar to most scientists, tiut with many audiences either mode. of presentation requires explanation; . Ir the cöre message deals with the most likely event, or the average condition, pdfs seem to focus attention better on that point.· If the core inessage is the probability of an extreme event, ogives föeus attention on the shape of the distribution; • in The difference is clear an. example I fudged from the hake forecasiing model. Consider cumulative catch over 20 years. From the pdf (Fig 9b);. the mode of test 2 is clearly at higher catches thari the mode of test 1. We are used to makirig decisions basect on differences iri the peak: of a pdf. Many would irifer fishing patterns producing test 2 are better. However, due to the skew and spread of the distributiön of forecasted catches; such a conclusion is unwarranted. The cfd (Fig 9a) shows that the mode. is not representative of the "average" condition. In fact, the medians and means differ very little. Do we conclude the tests produce the same catches? Th6 cfd shows the scenarios do differ: Test 1 has a higher likelihood of prOducing the larger catches.. Although producing large catches is not generally viewed as a risk, the communication issue is appropriate.. Both graphs show the same information, of course. Norietheless, ogives cäri highlight the tails of the distributions. When managers seleet among options to avoid risks, or to encourage unlikely events, ogives may be apfuticularly effective communicatiori tool.· 'C.M. 1993/D:11 Sess.P " Page 8 ICES STATUTORY MEETING 1993 . f f II , . LITERATURE CITED I I Boutillier, J.A., W. R. Harling and D. E. Yoimg. 1990~ W. E. RICKER Shrimp survey 88-S-1~ W~st .Co~t of Vanco~ver Island, April 28-May 8" 1988. Can. Däta Rep. Fish~ Aquat. SCI. 808. 40 p. , . ' . ' l : ! Carscadden; J.E., K.T. Frank, and D.S. Mhler. 1989. Capelin (Mai/olus villosuS) späwning on the Southeast Shoal: influence of physicäl factors past and present: Can.. J. Fish. Aquat. Sei. 46: 1743-1754. •I ' Dom, M. W~ and R.D. Methot. 1992 stätus of th coastaI Pacific whiting resource in 1992. in . Pacific Fishery Management Council, Status of the Pacific Coast groundfish fishery through 1992 and recommended acceptable biological catches in 1993; p. AI-A58. (Document prepared for the Council and" its advisory entiÜes) Pacific Fisheries Management Councii, Metro Center, Suite 420J 2000 SW First Ave. Portland, OR. " , , I , " , Evans, G.T and J.C. Rice. ,1988. Predicting recruitment from stock siie without the mediation öf a functionäl' relation. J. Cons. int. Exp. Mer, 44: 1 i 1-122. .' , Evans, G.T., J.C.Rice, and S.A. Akenhead. ms. The probability distribution for abundance of fish, and its pattern in space. ; , , , . I ,. I ': ".,,' ICNAF. 1977. Redbook 1977:, Standing Committee on~Research and Statistics. Proceedings of . special meeting December 1976 and annual meeting,May-June 1977~ Dartmouth N.S. I "' ' Canada' , I Rice, J.C., in press. Forecasting abundance from habidi Ineasures using nonparametri6 density ,estimatiori' methods. Can. J. Fish Aquat. ScL 50.xxx-xxx. , Rice~ , " I ic. and' G~T. Evans. 1988. Tools for ernbracing unceItairity in the m~agement of the cod fishery in NAFO divisions 2J+3KL. J. Cons. int. Exp. Mer 45:73-81. I' Richards, L.J. 1991. Use of contradictory data soJces in stock assessments. 11:225-238.,' , , / , , Fish. Res. I Ricker; \V.E~ 1954. Stock and recruitment. J. Fish. r~s. Bd. Can. ,11:559-623.. , " ! Schnute, J.T. and R. Hilbom. iri press. Analysis of contradictory data sources in fish stock assessrrierit. Can. ]. Fish. Aquat. Sei. xx:xxx-xxx. ! ~ Swartzman, G.L., W.M. Geti, R.C~ Frands, R.T~ Haar, and K. Rose. 1983. A management analysis of the Pacific whiting (Merluccitis productus) fishery usirig an age-structurecI stochastic recruitment model. Can. J~ Fish. Aquat. ScL 40:524-539~ ", • ,."" ' " , I ", . ','. ' • ICES STATUTORY MEETING 1993 C.M. 1993/D: 11 Sess.P Page 9 Walters, C.J. 1985. Bias in the estimation of functional relationships form time series data. Can. J. Fish. Aquat. Sci. 42:147-149. Walters, C.J. and D.L. Ludwig. 1981. Effects of measurement errors on the assessment of stock-recruitment relationships. Can. J. Fish. Aquat. Sci. 38:704-710. FIGURE LEGENDS • • .. Fig. 1. Scatter plot of recruits (#'s at age 4) vS. ssb for eod in NAFO Div. 2J3KL from 1962 - 1977 (see Rice and Evans 1988). Fig 2. Ogives of SSB estimated from 200 independent simulations, starting with 1977 conditions and proceeding 10 years: a) F= 0.16, using a very large value for "0" (no stock-recruit relationship) or "0" tuned with data in Fig. 1; b) tuned "0" and F increasing from 0.16 to 0.52 in steps of 0.03. Fig 3. Scatter plot of recruits (#'s at age 2) vs ssb for Pacifie hake, using data from Dorn and Methot 1992. Fig 4. Recruitments of Pacific Hake stock and fishery over 100 years; population parameters from table 1. a) Time series of recruits averaged over 200 independent simulations. b) Ln frequency of occurrence (y-axis) of cohorts of various sizes (x-axis); from 200 siniulations, each of 100 years. Fig 5. As in Fig 4a, but for a) catch, and b) SSB. Fig 6. Ogive of a) catches and b) SSb, after 20 years, from 200 simulations of Pacific hake stock and fishery (Fig 4), Fig. 7. Scatter plot of capelin density (arbitrary hydroacoustie units) vs bottom temperature, from survey of NAFO Div. 3LNO in 1987 with linear and polynomial regression lines. Fig 8. Ogives of density of capelin for 4 trial values of bottom temperature; data from Fig. 7, and tuned Cauchy algorithm. Fig 9. Forc:~cast cumulative catches of hake over 20 years, for two test fishing scenarios (details are artificial; to produce desired pattern of frequencies for example). a) Results displayed as ogive (efd), b) results displayed as pdf. TABLE 1. population parameters input to hake simulation model. AGE 2' 3 o.ta from the 11192 .. llllment POPAC' 0.678' 0.528 NMORT 0.237 0.237 POPWT0.278 0.371 4 5 8 7 0.042' 0.237 0.448 0.476 0.2370.531 0.475 0.237 0.575 0.064 0.2370.628 - 0.97 MATURE 0.19 0.&4' o.n' 0.82 0.D3 USSLCT CANSLCT 0.04 0' 0.15 0.51 ' 0.<42 0.56 0.73 0.81 0.92 0.67 IPROPFEM 0.48 - 0.512 0.52 0.524~ O.~ 0.878 0.763-0.654 0.828 0.860 0.801 0.GG4: 0.678. 0.875 ; 0.501 Exper'rm«lUII cetch Ill-oe veotore (MIeetIvItIM), 0.037 0.150 0.417 Vounger 0.053 0.213 : 0.514 0.145 0Ider 0.036 0.403 Aeeeaament POPAC NMORT POPW'T, MATURE USSLCT CANSLCT ~ • 0.98: 0.74- 8 0 0.237: 0.666 10· 0.454 0.237 0.678 1 1 1 0.8 0.99 0.88 0.529 0.538 0.818 _0.887 0.886 0.828 0.878 0.801; 0.008 0.237 0.694 12- 11 0.002 _ 0.2370.75 14 13 0.158; 0.237: 0.88' 0.002 0.237, 0.n8 0.005: 0_237 0.967' 15- 0.067. 0.237 1.047 ,1.' , 1 0.97 " 0.95 0.88 1 0.58 0.94 0.24 0.68 0.06 . 0.32 _ 0.01 0.1 0.539 0.544 - 0.l553 0.M1 0.!568 0.575 0.880" 0.860 0.919 0.810 0.763 0.967 0.701' 0.514 0.410 0.213 O.9OQ'· o.~ 0.163' 0.053, 0.310' 0.047. 0.009 0.097 ln/tIaI populelon vector (blUionI) Naua! mortaUtv rate •. PopulatIon -'ght IllIlQ8 (Kg) , • Propor1Ion of eexuaIIV ma1ure tem.Iee U.S.l\ehery eeIectMty et age. • Canadlen fIeh«y eeIec1IvIty 1ll1lQ8. • Total flehety eeIec1Mty et 1lQ8. .- .·--.-Vounger·---.· F1ehingeelec1lvltytoryoungerlleh _ _ • 0Ider • F1ehing aeIec1Ivity for oIder fleh "'_" . . ~ •__. .' ._ II -. - I I, TABLE'2. Years . 0 0 25 26 28 21 21 25 50 100 125 150 175 200 • Younger. Catch; 0 75 Over 200 simulations of hake moder, tabulation of.tl:t e number,of years thatthe SSB;was;below.the cr~tl.cal value used by.managers to indicate need to apply' conservative-exploitaiton rates. Control; Catch, 22. 22 15 45. Older Catch 1 25 22 29 27 19 16 21 19 51 23 15 18 26 23 39 900 800 ....fit C 0 FIG 1 .-- 700 -E 600 . '-" 500 3 '(J CD cx 400 300 200 1913 100 o • .25 .5 .75 SSB (mmt) 1 1.25 Projected SSB of Cod After 10 Years F-0.16 200~-----------------------' ....., Larp "Ir •••• 'I'uDed "D" - . 150 ,.o. .•.•. ..• .• .- ..• ,: , ,, " 100 : .. . .. . ..,,. •. - FIG 2A • ,.' ,' 50 ' . .. ." . . .. ' ' o +-----""""""'i~~--...r.;....-..+-.•-••-.'- - - - - 1 - - - - - - - 1 2.0 1.5 1.0 0.5 0.0 SSB (mmt) ~oo .-------~--':":_:_::::;_.~-=:i:I_---= . !. I' __ FIG 100 E :J (..) OL.--"raa~u.&:::;"c.::.._::;;o.a.-I. o .25 .5 __J~ .75 SSB (mmt) .1_ 1 ....J 1.25 2a Recruits vs Spawning Biomass Pacific Whiting 1979 - 1991 10 • a.".... I'J -......= CI • 0 6 ,0 FIG 3 C +J E 4 CJ " • ~ • 2 0 0.0 I I 0.5 . • • ..a. ~ 'W' 1.0 SSB (mmt) ..... ,., I 1.5 2.0 \ 1 - . .... ...... ~_ .. I I I j j, . Number Recruita va Time (averaged over 200 runs) Paci1ic Whiting - fram' model farecasts ! 2.0 ~-.-;...---.-;....-;...;...-.----------------, l FIG 4A J II t 1.5 1.0 • .Ale Compoll1Ucm 0.5 Assessment - - Yo1ui&er Older -T-----+-----------f-----.-;...-~ 0.0 -+- o 100 I I Year;, 50 200 150 I 1 I I I I •I Frequency Distribution of Recruits Pacific Whlting - from model forecaats ! • 10 FIG 4B - 8 ~ () d CD & ... ......, 6 CD $.4' e::t 4 iie ComposlttoD - Aatl10811m8Dt - - YO\1Dl8r Older 2 ..... 0 0 1 2 3 4- 5 6 II Recruits (bi;llions) I 7 B 9 ~ Catch Over Time (averaged over 200 runs) Pacific Whiting - from model forecasts 0.225 Ale ComposlUon FIG 5A - klsessment - -Youna er .... Older 0.200 'Z' -~ .d 0.175 Q ~. «S tJ .e 0.150 0.125 +----+---+---I----t---+---+---t---; 200 175 125 150 75 100 25 50 o Year SSB over Time (averaged over 200 runs) Pacüic Whiting - from model forecasts • 0.45~---------------~-----, Ale CompoelUon - Aaseument. - -Youna er ...• Older FIG SB 0.40 0.35 0.30 0.25 0.20 -+-----.;.-----.------+-------1 o 50 100 150 200 Year CDF of Catch After 20 Years Pacific Whiting - from forecasting model 200 -r-------"::::::J"I-----, >. g 160 Q,) 50 ~ 120 FIG 6A lil:. .-...> Q,) «' '3 80 S § 40 u - Seleclivity Assessment • .••. Younger - Older O-l--l.--+--+-----t---+----I 1.0 0.2 0.4 0.6 0.8 0.0 Catch (millions tons) Spawning Biomass after 20 years Pacific Whiting - trom torecasting model 200 • -r---------=_--, >. () t::: 160 Q,) ;:3 0- ~ 120 ~ .-.... FIG 6a Q,) > «l ;; 8 e ;:3 u 80 Seleclivity 40 - Assessment .••• Younger - Older 0+.L.--1--+---+--~_+--+--+-_I 0.0 0.2 0.4 0.6 0.8 1.0 1.2 1.4 1.6 SSB (millions tons) 1987 Cape1in Density vs. Bottom Temperature , (/) 125 .+J R-square R-square c :J = 0.361 = 0.28 I u 0 .+J r.n ::J 0 FIG 7 a u 0 0 0 0 ~ '1J I 0 0 ~ ... .- 8 0 a ..' .... 0 .' -erc]" 2.0 ~ .0 ~ . .. .. .. 0 ~ « ... 0 -2.0 0.0 a 6.0 4.0 Degree (C) 1.0 ~--===~_~_:""':_~_~-"="'-'='"._~_::-:_:-:_:"""ll_~-r----~":",:,,". . ~,,,~,'~;o:-:-:-"-I I ,, c o --toJ I 0.8 , , ~ • FIG a , o a. o 0.6 I I I ~ CL .+J .... I ", - .... .. _..I I I.···· .. 0.4 o :1 " ' _ :, ,. ...r ::J E ..... " , .... .... .... .... I Cl) .> I .. I I 0.2 =' () 0.0 . o' _0 .-0' _.,-" ,._,,1 .--"~ S.S·C 3.S·C :," ~ ~ 0 . 20 40 60 , .S·C -O.S·C 80 Capelin Density (Hydroacoustic Units) 100 Cummulalive Catch from model forecasts 500 - r - - - - - - - - - - - - - - -.,...:"...:"" ,. .- =-------, .-..~ ...' ......'..'..' ..' Fig. 9a ........ 400 .... .. .' ~ u 500 = ." .'" Ai. Compol1t1on - Test 1 .. .. rest 2 ... .... ' ' ' Q) & r: 200 Q) 100 0 0.0 2.0 4.0 6.0 10.0 8.0 Cummulative Catcb (mmt) Cnmmulative Catch from model forecasts Fig. 9b _. Compoaticm 15 - Teilt 1 .... Test 2 ~ (J s:= 10 .: Q) & Q) ~ ö ···· · · 0 0.0 2.0 4.0 6.0 Cummulative Catch (mmt) 8.0 10.0