Author Archives: Mayo

Mementos from Excursion 4: Objectivity & Auditing: Blurbs of Tours I – IV

Posted on January 13, 2019 by Mayo

Excursion 4: Objectivity and Auditing (blurbs of Tours I – IV)

 

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Excursion 4 Tour I: The Myth of “The Myth of Objectivity”

Blanket slogans such as “all methods are equally objective and subjective” trivialize into oblivion the problem of objectivity. Such cavalier attitudes are at odds with the moves to take back science The goal of this tour is to identify what there is in objectivity that we won’t give up, and shouldn’t. While knowledge gaps leave room for biases and wishful thinking, we regularly come up against data that thwart our expectations and disagree with predictions we try to foist upon the world. This pushback supplies objective constraints on which our critical capacity is built. Supposing an objective method is to supply formal, mechanical, rules to process data is a holdover of a discredited logical positivist philosophy.Discretion in data generation and modeling does not warrant concluding: statistical inference is a matter of subjective belief. It is one thing to talk of our models as objects of belief and quite another to maintain that our task is to model beliefs. For a severe tester, a statistical method’s objectivity requires the ability to audit an inference: check assumptions, pinpoint blame for anomalies, falsify, and directly register how biasing selection effects–hunting, multiple testing and cherry-picking–alter its error probing capacities.

Keywords

objective vs. subjective, objectivity requirements, auditing, dirty hands argument, phenomena vs. epiphenomena, logical positivism, verificationism, loss and cost functions, default Bayesians, equipoise assignments, (Bayesian) wash-out theorems, degenerating program, transparency, epistemology: internal/external distinction

 

Excursion 4 Tour II: Rejection Fallacies: Whose Exaggerating What?

We begin with the Mountains out of Molehills Fallacy (large n problem): The fallacy of taking a (P-level) rejection of H0 with larger sample size as indicating greater discrepancy from H0 than with a smaller sample size. (4.3). The Jeffreys-Lindley paradox shows with large enough n, a .05 significant result can correspond to assigning H0 a high probability .95. There are family feuds as to whether this is a problem for Bayesians or frequentists! The severe tester takes account of sample size in interpreting the discrepancy indicated. A modification of confidence intervals (CIs) is required.

It is commonly charged that significance levels overstate the evidence against the null hypothesis (4.4, 4.5). What’s meant? One answer considered here, is that the P-value can be smaller than a posterior probability to the null hypothesis, based on a lump prior (often .5) to a point null hypothesis. There are battles between and within tribes of Bayesians and frequentists. Some argue for lowering the P-value to bring it into line with a particular posterior. Others argue the supposed exaggeration results from an unwarranted lump prior to a wrongly formulated null.We consider how to evaluate reforms based on bayes factor standards (4.5). Rather than dismiss criticisms of error statistical methods that assume a standard from a rival account, we give them a generous reading. Only once the minimal principle for severity is violated do we reject them. Souvenir R summarizes the severe tester’s interpretation of a rejection in a statistical significance test. At least 2 benchmarks are needed: reports of discrepancies (from a test hypothesis) that are, and those that are not, well indicated by the observed difference.

Keywords

significance test controversy, mountains out of molehills fallacy, large n problem, confidence intervals, P-values exaggerate evidence, Jeffreys-Lindley paradox, Bayes/Fisher disagreement, uninformative (diffuse) priors, Bayes factors, spiked priors, spike and slab, equivocating terms, severity interpretation of rejection (SIR)

 

Excursion 4 Tour III: Auditing: Biasing Selection Effects & Randomization

Tour III takes up Peirce’s “two rules of inductive inference”: predesignation (4.6) and randomization (4.7). The Tour opens on a court case transpiring: the CEO of a drug company is being charged with giving shareholders an overly rosy report based on post-data dredging for nominally significant benefits. Auditing a result includes checking for (i) selection effects, (ii) violations of model assumptions, and (iii) obstacles to moving from statistical to substantive claims. We hear it’s too easy to obtain small P-values, yet replication attempts find it difficult to get small P-values with preregistered results. I call this the paradox of replication. The problem isn’t P-values but failing to adjust them for cherry picking and other biasing selection effects. Adjustments by Bonferroni and false discovery rates are considered. There is a tension between popular calls for preregistering data analysis, and accounts that downplay error probabilities. Worse, in the interest of promoting a methodology that rejects error probabilities, researchers who most deserve lambasting are thrown a handy line of defense. However, data dependent searching need not be pejorative. In some cases, it can improve severity. (4.6)

Big Data cannot ignore experimental design principles. Unless we take account of the sampling distribution, it becomes difficult to justify resampling and randomization. We consider RCTs in development economics (RCT4D) and genomics. Failing to randomize microarrays is thought to have resulted in a decade lost in genomics. Granted the rejection of error probabilities is often tied to presupposing their relevance is limited to long-run behavioristic goals, which we reject. They are essential for an epistemic goal: controlling and assessing how well or poorly tested claims are. (4.7)

Keywords

error probabilities and severity, predesignation, biasing selection effects, paradox of replication, capitalizing on chance, bayes factors, batch effects, preregistration, randomization: Bayes-frequentist rationale, bonferroni adjustment, false discovery rates, RCT4D, genome-wide association studies (GWAS)

 

Excursion 4 Tour IV: More Auditing: Objectivity and Model Checking

While all models are false, it’s also the case that no useful models are true. Were a model so complex as to represent data realistically, it wouldn’t be useful for finding things out. A statistical model is useful by being adequate for a problem, meaning it enables controlling and assessing if purported solutions are well or poorly probed and to what degree. We give a way to define severity in terms of solving a problem.(4.8) When it comes to testing model assumptions, many Bayesians agree with George Box (1983) that “it requires frequentist theory of significance tests” (p. 57). Tests of model assumptions, also called misspecification (M-S) tests, are thus a promising area for Bayes-frequentist collaboration. (4.9) When the model is in doubt, the likelihood principle is inapplicable or violated. We illustrate a non-parametric bootstrap resampling. It works without relying on a theoretical  probability distribution, but it still has assumptions. (4.10). We turn to the M-S testing approach of econometrician Aris Spanos.(4.11) I present the high points for unearthing spurious correlations, and assumptions of linear regression, employing 7 figures. M-S tests differ importantly from model selection–the latter uses a criterion for choosing among models, but does not test their statistical assumptions. They test fit rather than whether a model has captured the systematic information in the data.

Keywords

adequacy for a problem, severity (in terms of problem solving), model testing/misspecification (M-S) tests, likelihood principle conflicts, bootstrap, resampling, Bayesian p-value, central limit theorem, nonsense regression, significance tests in model checking, probabilistic reduction, respecification

 

Where you are in the Journey 

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Excerpt from Excursion 4 Tour II: 4.4 “Do P-Values Exaggerate the Evidence?”

Posted on January 10, 2019 by Mayo

getting beyond…

Excerpt from Excursion 4 Tour II*

 

4.4 Do P-Values Exaggerate the Evidence?

“Significance levels overstate the evidence against the null hypothesis,” is a line you may often hear. Your first question is:

What do you mean by overstating the evidence against a hypothesis?

Several (honest) answers are possible. Here is one possibility:

What I mean is that when I put a lump of prior weight π0 of 1/2 on a point null H0 (or a very small interval around it), the P-value is smaller than my Bayesian posterior probability on H0.

More generally, the “P-values exaggerate” criticism typically boils down to showing that if inference is appraised via one of the probabilisms – Bayesian posteriors, Bayes factors, or likelihood ratios – the evidence against the null (or against the null and in favor of some alternative) isn’t as big as 1 − P.

You might react by observing that: (a) P-values are not intended as posteriors in H0 (or Bayes ratios, likelihood ratios) but rather are used to determine if there’s an indication of discrepancy from, or inconsistency with, H0. This might only mean it’s worth getting more data to probe for a real effect. It’s not a degree of belief or comparative strength of support to walk away with. (b) Thus there’s no reason to suppose a P-value should match numbers computed in very different accounts, that differ among themselves, and are measuring entirely different things. Stephen Senn gives an analogy with “height and stones”:

. . . [S]ome Bayesians in criticizing P-values seem to think that it is appropriate to use a threshold for significance of 0.95 of the probability of the alternative hypothesis being true. This makes no more sense than, in moving from a minimum height standard (say) for recruiting police officers to a minimum weight standard, declaring that since it was previously 6 foot it must now be 6 stone. (Senn 2001b, p. 202)

To top off your rejoinder, you might ask: (c) Why assume that “the” or even “a” correct measure of evidence (relevant for scrutinizing the P-value) is one of the probabilist ones?

All such retorts are valid, and we’ll want to explore how they play out here. Yet, I want to push beyond them. Let’s be open to the possibility that evidential measures from very different accounts can be used to scrutinize each other.

Getting Beyond “I’m Rubber and You’re Glue”. The danger in critiquing statistical method X from the standpoint of the goals and measures of a distinct school Y, is that of falling into begging the question. If the P-value is exaggerating evidence against a null, meaning it seems too small from the perspective of school Y, then Y’s numbers are too big, or just irrelevant, from the perspective of school X. Whatever you say about me bounces off and sticks to you. This is a genuine worry, but it’ s not fatal. The goal of this journey is to identify minimal theses about “ bad evidence, no test (BENT)” that enable some degree of scrutiny of any statistical inference account – at least on the meta-level. Why assume all schools of statistical inference embrace the minimum severity principle? I don’t, and they don’t. But by identifying when methods violate severity, we can pull back the veil on at least one source of disagreement behind the battles.

Thus, in tackling this latest canard, let’ s resist depicting the critics as committing a gross blunder of confusing a P-value with a posterior probability in a null. We resist, as well, merely denying we care about their measure of support. I say we should look at exactly what the critics are on about. When we do, we will have gleaned some short-cuts for grasping a plethora of critical debates. We may even wind up with new respect for what a P-value, the least popular girl in the class, really does.

To visit the core arguments, we travel to 1987 to papers by J. Berger and Sellke, and Casella and R. Berger. These, in turn, are based on a handful of older ones (Cox 1977, E, L, & S 1963, Pratt 1965), and current discussions invariably revert back to them. Our struggles through quicksand of Excursion 3, Tour II, are about to pay large dividends.

This excerpt comes from Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars (Mayo, CUP 2018).

 Readers can find blogposts that trace out the discussion of this topic, as I was developing it, along with comments. The following 2 are central:

(7/14) “P-values overstate the evidence against the null”: legit or fallacious? (revised) 71 comments

(7/23) Continued:”P-values overstate the evidence against the null”: legit or fallacious? 39 comments

 

Earlier excerpts and mementos from SIST up to Dec 31, 20018 are here.

Where you are in the journey.

 

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January Invites: Ask me questions (about SIST), Write Discussion Analyses (U-Phils)

Posted on January 5, 2019 by Mayo

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ASK ME. Some readers say they’re not sure where to ask a question of comprehension on Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars (2018, CUP)–SIST– so here’s a special post to park your questions of comprehension (to be placed in the comments) on a little over the first half of the book. That goes up to and includes Excursion 4 Tour I on “The Myth of ‘The Myth of Objectivity'”. However,I will soon post on Tour II: Rejection Fallacies: Who’s Exaggerating What? So feel free to ask questions of comprehension as far as p.259.

All of the SIST BlogPost (Excerpts and Mementos) so far are here.

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WRITE A DISCUSSION NOTE: Beginning January 16, anyone who wishes to write a discussion note (on some aspect or issue up to p. 259 are invited to do so (<750 words, longer if you wish). Send them to my error email.  I will post as many as possible on this blog.

We initially called such notes “U-Phils” as in “You do a Philosophical analysis”, which really only means it’s an analytic excercize that strives to first give the most generous interpretation to positions, and then examines them. See the general definition of  a U-Phil.

Some Examples:

Mayo, Senn, and Wasserman on Gelman’s RMM** Contribution

U-Phil: A Further Comment on Gelman by Christian Hennig.

For a whole group of reader contributions, including Jim Berger on Jim Berger, see: Earlier U-Phils and Deconstructions

If you’re writing a note on objectivity, you might wish to compare and contrast Excursion 4 Tour I with a paper by Gelman and Hennig (2017): “Beyond subjective and objective in Statistics”.

These invites extend through January.

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SIST* Blog Posts: Excerpts & Mementos (to Dec 31 2018)

Posted on January 3, 2019 by Mayo

Surveying SIST Blog Posts So Far

Excerpts

  • 05/19: The Meaning of My Title: Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars
  • 09/08: Excursion 1 Tour I: Beyond Probabilism and Performance: Severity Requirement (1.1)
  • 09/11: Excursion 1 Tour I (2nd stop): Probabilism, Performance, and Probativeness (1.2)
  • 09/15: Excursion 1 Tour I (3rd stop): The Current State of Play in Statistical Foundations: A View From a Hot-Air Balloon (1.3)
  • 09/29: Excursion 2: Taboos of Induction and Falsification: Tour I (first stop)
  • 10/10: Excursion 2 Tour II (3rd stop): Falsification, Pseudoscience, Induction (2.3)
  • 11/30: Where are Fisher, Neyman, Pearson in 1919? Opening of Excursion 3
  • 12/01: Neyman-Pearson Tests: An Episode in Anglo-Polish Collaboration: Excerpt from Excursion 3 (3.2)
  • 12/04: First Look at N-P Methods as Severe Tests: Water plant accident [Exhibit (i) from Excursion 3]
  • 12/11: It’s the Methods, Stupid: Excerpt from Excursion 3 Tour II  (Mayo 2018, CUP)
  • 12/20: Capability and Severity: Deeper Concepts: Excerpts From Excursion 3 Tour III
  • 12/26: Excerpt from Excursion 4 Tour I: The Myth of “The Myth of Objectivity” (Mayo 2018, CUP)
  • 12/29: 60 Years of Cox’s (1958) Chestnut: Excerpt from Excursion 3 tour II.

Mementos, Keepsakes and Souvenirs

  • 10/29: Tour Guide Mementos (Excursion 1 Tour II of How to Get Beyond the Statistics Wars)
  • 11/8:   Souvenir C: A Severe Tester’s Translation Guide (Excursion 1 Tour II)
  • 10/5:  “It should never be true, though it is still often said, that the conclusions are no more accurate than the data on which they are based” (Keepsake by Fisher, 2.1)
  • 11/14: Tour Guide Mementos and Quiz 2.1 (Excursion 2 Tour I Induction and Confirmation)
  • 11/17: Mementos for Excursion 2 Tour II Falsification, Pseudoscience, Induction
  • 12/08: Memento & Quiz (on SEV): Excursion 3, Tour I
  • 12/13: Mementos for “It’s the Methods, Stupid!” Excursion 3 Tour II (3.4-3.6)
  • 12/26: Tour Guide Mementos From Excursion 3 Tour III: Capability and Severity: Deeper Concepts

*Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars (Mayo, CUP 2018).

Categories: SIST, Statistical Inference as Severe Testing | Leave a comment

Mayo-Spanos Summer Seminar PhilStat: July 28-Aug 11, 2019: Instructions for Applying Now Available

Posted on January 2, 2019 by Mayo

INSTRUCTIONS FOR APPLYING ARE NOW AVAILABLE

See the Blog at SummerSeminarPhilStat

Categories: Announcement, Error Statistics, Statistics | Leave a comment

Midnight With Birnbaum (Happy New Year 2018)

Posted on December 31, 2018 by Mayo

 Just as in the past 7 years since I’ve been blogging, I revisit that spot in the road at 9p.m., just outside the Elbar Room, look to get into a strange-looking taxi, to head to “Midnight With Birnbaum”. (The pic on the left is the only blurry image I have of the club I’m taken to.) I wonder if the car will come for me this year, as I wait out in the cold, now that Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars (STINT) is out. STINT doesn’t rehearse the argument from my Birnbaum article, but there’s much in it that I’d like to discuss with him. The (Strong) Likelihood Principle–whether or not it is named–remains at the heart of many of the criticisms of Neyman-Pearson (N-P) statistics (and cognate methods). 2018 was the 60th birthday of Cox’s “weighing machine” example, which was the basis of Birnbaum’s attempted proof. Yet as Birnbaum insisted, the “confidence concept” is the “one rock in a shifting scene” of statistical foundations, insofar as there’s interest in controlling the frequency of erroneous interpretations of data. (See my rejoinder.) Birnbaum bemoaned the lack of an explicit evidential interpretation of N-P methods. Maybe in 2019? Anyway, the cab is finally here…the rest is live. Happy New Year!

You know how in that Woody Allen movie, “Midnight in Paris,” the main character (I forget who plays it, I saw it on a plane) is a writer finishing a novel, and he steps into a cab that mysteriously picks him up at midnight and transports him back in time where he gets to run his work by such famous authors as Hemingway and Virginia Wolf?  (It was a new movie when I began the blog in 2011.) He is wowed when his work earns their approval and he comes back each night in the same mysterious cab…Well, imagine an error statistical philosopher is picked up in a mysterious taxi at midnight (New Year’s Eve 2011 2012, 2013, 2014, 2015, 2016, 2017, 2018) and is taken back sixty years and, lo and behold, finds herself in the company of Allan Birnbaum.[i] There are a number of 2018 updates.

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ERROR STATISTICIAN: It’s wonderful to meet you Professor Birnbaum; I’ve always been extremely impressed with the important impact your work has had on philosophical foundations of statistics.  I happen to be writing on your famous argument about the likelihood principle (LP).  (whispers: I can’t believe this!)

BIRNBAUM: Ultimately you know I rejected the LP as failing to control the error probabilities needed for my Confidence concept. But you know all this, I’ve read it in your new book: Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars (STINT, 2018, CUP).

ERROR STATISTICIAN: You’ve read my new book? Wow! Then you know I don’t think your argument shows that the LP follows from such frequentist concepts as sufficiency S and the weak conditionality principle WLP. I don’t rehearse my argument there, but I first found it in 2006.[ii]  Sorry,…I know it’s famous…

BIRNBAUM:  Well, I shall happily invite you to take any case that violates the LP and allow me to demonstrate that the frequentist is led to inconsistency, provided she also wishes to adhere to the WLP and sufficiency (although less than S is needed).

ERROR STATISTICIAN: Well I show that no contradiction follows from holding WCP and S, while denying the LP.

BIRNBAUM: Well, well, well: I’ll bet you a bottle of Elba Grease champagne that I can demonstrate it!

ERROR STATISTICAL PHILOSOPHER:  It is a great drink, I must admit that: I love lemons.

BIRNBAUM: OK.  (A waiter brings a bottle, they each pour a glass and resume talking).  Whoever wins this little argument pays for this whole bottle of vintage Ebar or Elbow or whatever it is Grease.

ERROR STATISTICAL PHILOSOPHER:  I really don’t mind paying for the bottle.

BIRNBAUM: Good, you will have to. Take any LP violation. Let  x’ be 2-standard deviation difference from the null (asserting μ = 0) in testing a normal mean from the fixed sample size experiment E’, say n = 100; and let x” be a 2-standard deviation difference from an optional stopping experiment E”, which happens to stop at 100.  Do you agree that:

(0) For a frequentist, outcome x’ from E’ (fixed sample size) is NOT evidentially equivalent to x” from E” (optional stopping that stops at n)

ERROR STATISTICAL PHILOSOPHER: Yes, that’s a clear case where we reject the strong LP, and it makes perfect sense to distinguish their corresponding p-values (which we can write as p’ and p”, respectively).  The searching in the optional stopping experiment makes the p-value quite a bit higher than with the fixed sample size.  For n = 100, data x’ yields p’= ~.05; while p”  is ~.3.  Clearly, p’ is not equal to p”, I don’t see how you can make them equal.

BIRNBAUM: Suppose you’ve observed x”, a 2-standard deviation difference from an optional stopping experiment E”, that finally stops at n=100.  You admit, do you not, that this outcome could have occurred as a result of a different experiment?  It could have been that a fair coin was flipped where it is agreed that heads instructs you to perform E’ (fixed sample size experiment, with n = 100) and tails instructs you to perform the optional stopping experiment E”, stopping as soon as you obtain a 2-standard deviation difference, and you happened to get tails, and performed the experiment E”, which happened to stop with n =100. 

ERROR STATISTICAL PHILOSOPHER:  Well, that is not how x” was obtained, but ok, it could have occurred that way.

BIRNBAUM:  Good. Then you must grant further that your result could have come from a special experiment I have dreamt up, call it a BB-experiment.  In a BB- experiment, if the outcome from the experiment you actually performed has an outcome with a proportional likelihood to one in some other experiment not performed, E’, then we say that your result has an “LP pair”.  For any violation of the strong LP, the outcome observed, let it be x”, has an “LP pair”, call it x’, in some other experiment E’.  In that case, a BB-experiment stipulates that you are to report x” as if you had determined whether to run E’ or E” by flipping a fair coin.

(They fill their glasses again)

ERROR STATISTICAL PHILOSOPHER: You’re saying that if my outcome from trying and trying again, that is, optional stopping experiment E”, with an “LP pair” in the fixed sample size experiment I did not perform, then I am to report x” as if the determination to run E” was by flipping a fair  coin (which decides between E’ and E”)?

BIRNBAUM: Yes, and one more thing. If your outcome had actually come from the fixed sample size experiment E’, it too would have  an “LP pair” in the experiment you did not perform, E”.  Whether you actually observed x” from E”, or x’ from E’, you are to report it as x” from E”.

ERROR STATISTICAL PHILOSOPHER: So let’s see if I understand a Birnbaum BB-experiment: whether my observed 2-standard deviation difference came from E’ or E” (with sample size n) the result is reported as x’, as if it came from E’ (fixed sample size), and as a result of this strange type of a mixture experiment.

BIRNBAUM: Yes, or equivalently you could just report x*: my result is a 2-standard deviation difference and it could have come from either E’ (fixed sampling, n= 100) or E” (optional stopping, which happens to stop at the 100th trial).  That’s how I sometimes formulate a BB-experiment.

ERROR STATISTICAL PHILOSOPHER: You’re saying in effect that if my result has an LP pair in the experiment not performed, I should act as if I accept the strong LP and just report it’s likelihood; so if the likelihoods are proportional in the two experiments (both testing the same mean), the outcomes are evidentially equivalent.

BIRNBAUM: Well, but since the BB- experiment is an imagined “mixture” it is a single experiment, so really you only need to apply the weak LP which frequentists accept.  Yes?  (The weak LP is the same as the sufficiency principle).

ERROR STATISTICAL PHILOSOPHER: But what is the sampling distribution in this imaginary BB- experiment?  Suppose I have Birnbaumized my experimental result, just as you describe, and observed a 2-standard deviation difference from optional stopping experiment E”.  How do I calculate the p-value within a Birnbaumized experiment?

BIRNBAUM: I don’t think anyone has ever called it that.

ERROR STATISTICAL PHILOSOPHER: I just wanted to have a shorthand for the operation you are describing, there’s no need to use it, if you’d rather I not.  So how do I calculate the p-value within a BB-experiment?

BIRNBAUM: You would report the overall p-value, which would be the average over the sampling distributions: (p’ + p”)/2

Say p’ is ~.05, and p” is ~.3; whatever they are, we know they are different, that’s what makes this a violation of the strong LP (given in premise (0)).

ERROR STATISTICAL PHILOSOPHER: So you’re saying that if I observe a 2-standard deviation difference from E’, I do not report  the associated p-value p’, but instead I am to report the average p-value, averaging over some other experiment E” that could have given rise to an outcome with a proportional likelihood to the one I observed, even though I didn’t obtain it this way?

BIRNBAUM: I’m saying that you have to grant that x’ from a fixed sample size experiment E’ could have been generated through a BB- experiment.

My this drink is sour!

ERROR STATISTICAL PHILOSOPHER: Yes, I love pure lemon.

BIRNBAUM: Perhaps you’re in want of a gene; never mind.

I’m saying you have to grant that x’ from a fixed sample size experiment E’ could have been generated through a BB-experiment.  If you are to interpret your experiment as if you are within the rules of a BB experiment, then x’ is evidentially equivalent to x” (is equivalent to  x*).  This is premise (1).

ERROR STATISTICAL PHILOSOPHER: But the result would be that the p-value associated with x’ (fixed sample size) is reported to be larger than it actually is (.05), because I’d be averaging over fixed and optional stopping experiments; while observing x” (optional stopping) is reported to be smaller than it is–in both cases because of an experiment I did not perform.

BIRNBAUM: Yes, the BB-experiment computes the P-value in an unconditional manner: it takes the convex combination over the 2 ways the result could have come about. 

ERROR STATISTICAL PHILOSOPHER: this is just a matter of your definitions, it is an analytical or mathematical result, so long as we grant being within your BB experiment.

BIRNBAUM: True, (1) plays the role of the sufficiency assumption, but one need not even appeal to this, it is just a matter of mathematical equivalence.

By the way, I am focusing just on LP violations, therefore, the outcome, by definition, has an LP pair.  In other cases, where there is no LP pair, you just report things as usual.

ERROR STATISTICAL PHILOSOPHER: OK, but p’ still differs from p”; so I still don’t how I’m forced to infer the strong LP which identifies the two. In short, I don’t see the contradiction with my rejecting the strong LP in premise (0).  (Also we should come back to the “other cases” at some point….)

BIRNBAUM: Wait! Don’t be so impatient; I’m about to get to step (2). Here, let’s toast to the new year: “To Elbar Grease!”

ERROR STATISTICAL PHILOSOPHER: To Elbar Grease!

BIRNBAUM:  So far all of this was step (1).

ERROR STATISTICAL PHILOSOPHER: : Oy, what is step 2?

BIRNBAUM:  STEP 2 is this: Surely, you agree, that once you know from which experiment the observed 2-standard deviation difference actually came, you ought to report the p-value corresponding to that experiment. You ought NOT to report the average (p’ + p”)/2  as you were instructed to do in the BB experiment.

This gives us premise (2a):

(2a) outcome x”, once it is known that it came from E”, should NOT be  analyzed as in a BB- experiment where p-values are averaged. The report should instead use the sampling distribution of the optional stopping test E”, yielding the p-value, p” (~.37). In fact, .37 is the value you give in STINT p. 44 (imagining the experimenter keeps taking 10 more). 

ERROR STATISTICAL PHILOSOPHER:  So, having first insisted I imagine myself in a Birnbaumized, I mean a BB-experiment, and report an average p-value, I’m now to return to my senses and “condition” in order to get back to the only place I ever wanted to be, i.e., back to where I was to begin with?

BIRNBAUM: Yes, at least if you hold to the weak conditionality principle WCP (of D. R. Cox)—surely you agree to this.

(2b) Likewise, if you knew the 2-standard deviation difference came from E’, then

x’ should NOT be deemed evidentially equivalent to x” (as in the BB experiment), the report should instead use the sampling distribution of fixed test E’, (.05).  

ERROR STATISTICAL PHILOSOPHER: So, having first insisted I consider myself in a BB-experiment, in which I report the average p-value, I’m now to return to my senses and allow that if I know the result came from optional stopping, E”, I should “condition” on and report p”.

BIRNBAUM: Yes.  There was no need to repeat the whole spiel.

ERROR STATISTICAL PHILOSOPHER: I just wanted to be clear I understood you. Of course,all of this assumes the model is correct or adequate to begin with.

BIRNBAUM: Yes, the SLP is a principle for parametric inference within a given model. So you arrive at (2a) and (2b), yes?

ERROR STATISTICAL PHILOSOPHER: OK, but it might be noted that unlike premise (1), premises (2a) and (2b) are not given by definition, they concern an evidential standpoint about how one ought to interpret a result once you know which experiment it came from. In particular, premises (2a) and (2b) say I should condition and use the sampling distribution of the experiment known to have been actually performed, when interpreting the result.

BIRNBAUM: Yes, and isn’t this weak conditionality principle WCP one that you happily accept?

ERROR STATISTICAL PHILOSOPHER: Well the WCP is defined for actual mixtures, where one flipped a coin to determine if E’ or E” is performed, whereas, you’re requiring I consider an imaginary Birnbaum mixture experiment, where the choice of the experiment not performed will vary depending on the outcome that needs an LP pair; and I cannot even determine what this might be until after I’ve observed the result that would violate the LP? I don’t know what the sample size will be ahead of time.

BIRNBAUM: Sure, but you admit that your observed x” could have come about through a BB-experiment, and that’s all I need.  Notice

(1), (2a) and (2b) yield the strong LP!

Outcome x” from E”(optional stopping that stops at n) is evidentially equivalent to x’ from E’ (fixed sample size n).

ERROR STATISTICAL PHILOSOPHER:  Clever, but your “proof” is obviously unsound; and before I demonstrate this, notice that the conclusion, were it to follow, asserts p’ = p”, (e.g.,  .05 = .3!), even though it is unquestioned that p’ is not equal to p”, that is because we must start with an LP violation (premise (0)).

BIRNBAUM: Yes, it is puzzling, but where have I gone wrong?

(The waiter comes by and fills their glasses; they are so deeply engrossed in thought they do not even notice him.)

ERROR STATISTICAL PHILOSOPHER: There are many routes to explaining a fallacious argument.  Here’s one.  What is required for STEP 1 to hold, is the denial of what’s needed for STEP 2 to hold:

Step 1 requires us to analyze results in accordance with a BB- experiment.  If we do so, true enough we get:

premise (1): outcome x” (in a BB experiment) is evidentially equivalent to outcome x’ (in a BB  experiment):

That is because in either case, the p-value would be (p’ + p”)/2

Step 2 now insists that we should NOT calculate  evidential import as if we were in a BB- experiment.  Instead we should consider the experiment from which the data actually came, E’ or E”:

premise (2a): outcome x” (in a BB experiment) is/should be evidentially equivalent to x” from E” (optional stopping that stops at n):  its p-value should be p”.

premise (2b): outcome x’ (within in a BB experiment) is/should be evidentially equivalent to x’ from E’ (fixed sample size):  its p-value should be p’.

If (1) is true, then (2a) and (2b) must be false!

If (1) is true and we keep fixed the stipulation of a BB experiment (which we must to apply step 2), then (2a) is asserting:

The average p-value (p’ + p”)/2  =  p’  which is false.

Likewise if (1) is true, then (2b) is asserting:

the average p-value (p’ + p”)/2  =  p”  which is false

Alternatively, we can see what goes wrong by realizing:

If (2a) and (2b) are true, then premise (1) must be false.

In short your famous argument requires us to assess evidence in a given experiment in two contradictory ways: as if we are within a BB- experiment (and report the average p-value) and also that we are not, but rather should report the actual p-value.

I can render it as formally valid, but then its premises can never all be true; alternatively, I can get the premises to come out true, but then the conclusion is false—so it is invalid.  In no way does it show the frequentist is open to contradiction (by dint of accepting S, WCP, and denying the LP).

BIRNBAUM: Yet some people still think it is a breakthrough (in favor of Bayesianism).

ERROR STATISTICAL PHILOSOPHER: I have a much clearer exposition of what goes wrong in your argument than I did in the discussion from 2010. There were still several gaps, and lack of a clear articulation of the WCP. In fact, I’ve come to see that clarifying the entire argument turns on defining the WCP. Have you seen my 2014 paper in Statistical Science?  The key difference is that in (2014), the WCP is stated as an equivalence, as you intended. Cox’s WCP, many claim, was not an equivalence, going in 2 directions. Slides from a presentation may be found on this blogpost. 

BIRNBAUM: Yes I have seen your 2014 paper, very clever! Your Rejoinder to some of the critics is gutsy, to say the least. Congratulations! I’ve also seen the slides on your blog.

ERROR STATISTICAL PHILOSOPHER: Thank you, I’m amazed you follow my blog! But look I must get your answer to a question before you leave this year.

 Sudden interruption by the waiter

WAITER: Who gets the tab?

BIRNBAUM: I do.  To Elbar Grease! And to your new book SIST! 

ERROR STATISTICAL PHILOSOPHER: To Elbar Grease! To finally finishing SIST in 2018! Happy New Year!

ERROR STATISTICAL PHILOSOPHER: I have one quick question, Professor Birnbaum, and I swear that whatever you say will be just between us, I won’t tell a soul. In your last couple of papers, you suggest you’d discovered the flaw in your argument for the LP. Am I right? Even in the discussion of your (1962)paper, you seemed to agree with Pratt that WCP can’t do the job you intend.

BIRNBAUM: Savage, you know, never got off my case about remaining at “the half-way house” of likelihood, and not going full Bayesian. Then I wrote the review about the Confidence Concept as the one rock on a shifting scene… Pratt thought the argument should instead appeal to a Censoring Principle (basically, it doesn’t matter if your instrument cannot measure beyond k units if the measurement you’re making is under k units.)

ERROR STATISTICAL PHILOSOPHER: Yes, but who says frequentist error statisticians deny the Censoring Principle? So back to my question, you disappeared before answering last year…I just want to know…you did see the flaw, yes?

WAITER: We’re closing now; shall I call you a taxicab?

BIRNBAUM: Yes.

ERROR STATISTICAL PHILOSOPHER: ‘Yes’, you discovered the flaw in the argument, or ‘yes’ to the taxi?

MANAGER: We’re closing now; I’m sorry you must leave.

ERROR STATISTICAL PHILOSOPHER: We’re leaving I just need him to clarify his answer….

Large group of people bustle past.

Prof. Birnbaum…? Allan? Where did he go? (oy, not again!)

Link to complete discussion: 

Mayo, Deborah G. On the Birnbaum Argument for the Strong Likelihood Principle (with discussion & rejoinder).Statistical Science 29 (2014), no. 2, 227-266.

stat-sci

 

 

[i] Many links on the strong likelihood principle (LP or SLP) and Birnbaum may be found by searching this blog. Good sources for where to start as well as historical background papers may be found in my last blogpost.

[ii] By the way, Ronald Giere gave me numerous original papers of yours.  They’re in files in my attic library. Some are in mimeo, others typed…I mean, obviously for that  time that’s what they’d be…now of course, oh never mind, sorry.

Categories: Birnbaum Brakes, strong likelihood principle | Tags: , , , | Leave a comment

You Should Be Binge Reading the (Strong) Likelihood Principle

Posted on December 30, 2018 by Mayo

 

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An essential component of inference based on familiar frequentist notions: p-values, significance and confidence levels, is the relevant sampling distribution (hence the term sampling theory, or my preferred error statistics, as we get error probabilities from the sampling distribution). This feature results in violations of a principle known as the strong likelihood principle (SLP). To state the SLP roughly, it asserts that all the evidential import in the data (for parametric inference within a model) resides in the likelihoods. If accepted, it would render error probabilities irrelevant post data.

SLP (We often drop the “strong” and just call it the LP. The “weak” LP just boils down to sufficiency)

For any two experiments E1 and E2 with different probability models f1, f2, but with the same unknown parameter θ, if outcomes x* and y* (from E1 and E2 respectively) determine the same (i.e., proportional) likelihood function (f1(x*; θ) = cf2(y*; θ) for all θ), then x* and y* are inferentially equivalent (for an inference about θ).

(What differentiates the weak and the strong LP is that the weak refers to a single experiment.)
Continue reading →

Categories: Error Statistics, Statistics, strong likelihood principle | 1 Comment

60 Years of Cox’s (1958) Chestnut: Excerpt from Excursion 3 Tour II (Mayo 2018, CUP)

Posted on December 29, 2018 by Mayo

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2018 marked 60 years since the famous weighing machine example from Sir David Cox (1958)[1]. It’s one of the “chestnuts” in the exhibits of “chestnuts and howlers” in Excursion 3 (Tour II) of my new book Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars (SIST). It’s especially relevant to take this up now, just before we leave 2018, for reasons that will be revealed over the next day or two. So, let’s go back to it, with an excerpt from SIST (pp. 170-173).

Exhibit (vi): Two Measuring Instruments of Different Precisions. Did you hear about the frequentist who, knowing she used a scale that’s right only half the time, claimed her method of weighing is right 75% of the time?

She says, “I flipped a coin to decide whether to use a scale that’s right 100% of the time, or one that’s right only half the time, so, overall, I’m right 75% of the time.” (She wants credit because she could have used a better scale, even knowing she used a lousy one.)

Basis for the joke: An N-P test bases error probability on all possible outcomes or measurements that could have occurred in repetitions, but did not. Continue reading →

Categories: Birnbaum, Statistical Inference as Severe Testing, strong likelihood principle | 2 Comments

Excerpt from Excursion 4 Tour I: The Myth of “The Myth of Objectivity” (Mayo 2018, CUP)

Posted on December 26, 2018 by Mayo

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Tour I The Myth of “The Myth of Objectivity”*

 

Objectivity in statistics, as in science more generally, is a matter of both aims and methods. Objective science, in our view, aims to find out what is the case as regards aspects of the world [that hold] independently of our beliefs, biases and interests; thus objective methods aim for the critical control of inferences and hypotheses, constraining them by evidence and checks of error. (Cox and Mayo 2010, p. 276)

Whenever you come up against blanket slogans such as “no methods are objective” or “all methods are equally objective and subjective” it is a good guess that the problem is being trivialized into oblivion. Yes, there are judgments, disagreements, and values in any human activity, which alone makes it too trivial an observation to distinguish among very different ways that threats of bias and unwarranted inferences may be controlled. Is the objectivity–subjectivity distinction really toothless, as many will have you believe? I say no. I know it’s a meme promulgated by statistical high priests, but you agreed, did you not, to use a bit of chutzpah on this excursion? Besides, cavalier attitudes toward objectivity are at odds with even more widely endorsed grass roots movements to promote replication, reproducibility, and to come clean on a number of sources behind illicit results: multiple testing, cherry picking, failed assumptions, researcher latitude, publication bias and so on. The moves to take back science are rooted in the supposition that we can more objectively scrutinize results – even if it’s only to point out those that are BENT. The fact that these terms are used equivocally should not be taken as grounds to oust them but rather to engage in the difficult work of identifying what there is in “objectivity” that we won’t give up, and shouldn’t. Continue reading →

Categories: Error Statistics, SIST, Statistical Inference as Severe Testing | 4 Comments

Tour Guide Mementos From Excursion 3 Tour III: Capability and Severity: Deeper Concepts

Posted on December 26, 2018 by Mayo

Excursion 3 Tour III:

A long-standing family feud among frequentists is between hypotheses tests and confidence intervals (CIs). In fact there’s a clear duality between the two: the parameter values within the (1 – α) CI are those that are not rejectable by the corresponding test at level α. (3.7) illuminates both CIs and severity by means of this duality. A key idea is arguing from the capabilities of methods to what may be inferred. CIs thereby obtain an inferential rationale (beyond performance), and several benchmarks are reported. Continue reading →

Categories: confidence intervals and tests, reforming the reformers, Statistical Inference as Severe Testing | Leave a comment

Capability and Severity: Deeper Concepts: Excerpts From Excursion 3 Tour III

Posted on December 20, 2018 by Mayo

Deeper Concepts 3.7, 3.8

Tour III Capability and Severity: Deeper Concepts

 

From the itinerary: A long-standing family feud among frequentists is between hypotheses tests and confidence intervals (CIs), but in fact there’s a clear duality between the two. The dual mission of the first stop (Section 3.7) of this tour is to illuminate both CIs and severity by means of this duality. A key idea is arguing from the capabilities of methods to what may be inferred. The severity analysis seamlessly blends testing and estimation. A typical inquiry first tests for the existence of a genuine effect and then estimates magnitudes of discrepancies, or inquires if theoretical parameter values are contained within a confidence interval. At the second stop (Section 3.8) we reopen a highly controversial matter of interpretation that is often taken as settled. It relates to statistics and the discovery of the Higgs particle – displayed in a recently opened gallery on the “Statistical Inference in Theory Testing” level of today’s museum. Continue reading →

Categories: confidence intervals and tests, Statistical Inference as Severe Testing | 2 Comments

Summer Seminar PhilStat: July 28-Aug 11, 2019 (ii)

Posted on December 16, 2018 by Mayo

First draft of PhilStat Announcement

 

Categories: Announcement, Error Statistics | 5 Comments

Mementos for “It’s the Methods, Stupid!” Excursion 3 Tour II (3.4-3.6)

Posted on December 13, 2018 by Mayo

some snapshots from Excursion 3 tour II.

 

 

 

 

 

 

Excursion 3 Tour II: It’s The Methods, Stupid

Tour II disentangles a jungle of conceptual issues at the heart of today’s statistics wars. The first stop (3.4) unearths the basis for a number of howlers and chestnuts thought to be licensed by Fisherian or N-P tests.* In each exhibit, we study the basis for the joke.  Together, they show: the need for an adequate test statistic, the difference between implicationary (i assumptions) and actual assumptions, and the fact that tail areas serve to raise, and not lower, the bar for rejecting a null hypothesis. (Additional howlers occur in Excursion 3 Tour III)

recommended: medium to heavy shovel 

Continue reading →

Categories: Statistical Inference as Severe Testing | Leave a comment

It’s the Methods, Stupid: Excerpt from Excursion 3 Tour II (Mayo 2018, CUP)

Posted on December 11, 2018 by Mayo

Tour II It’s the Methods, Stupid

There is perhaps in current literature a tendency to speak of the Neyman–Pearson contributions as some static system, rather than as part of the historical process of development of thought on statistical theory which is and will always go on. (Pearson 1962, 276)

This goes for Fisherian contributions as well. Unlike museums, we won’ t remain static. The lesson from Tour I of this Excursion is that Fisherian and Neyman– Pearsonian tests may be seen as offering clusters of methods appropriate for different contexts within the large taxonomy of statistical inquiries. There is an overarching pattern: Continue reading →

Categories: Error Statistics, Statistical Inference as Severe Testing | 4 Comments

Memento & Quiz (on SEV): Excursion 3, Tour I

Posted on December 8, 2018 by Mayo

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As you enjoy the weekend discussion & concert in the Captain’s Central Limit Library & Lounge, your Tour Guide has prepared a brief overview of Excursion 3 Tour I, and a short (semi-severe) quiz on severity, based on exhibit (i).*

 

We move from Popper through a gallery on “Data Analysis in the 1919 Eclipse tests of the General Theory of Relativity (GTR)” (3.1) which leads to the main gallery on the origin of statistical tests (3.2) by way of a look at where the main members of our statistical cast are in 1919: Fisher, Neyman and Pearson. From the GTR episode, we identify the key elements of a statistical test–the steps in E.S. Pearson’s opening description of tests in 3.2. The classical testing notions–type I and II errors, power, consistent tests–are shown to grow out of requiring probative tests. The typical (behavioristic) formulation of N-P tests came later. The severe tester breaks out of the behavioristic prison. A first look at the severity construal of N-P tests is in Exhibit (i). Viewing statistical inference as severe testing shows how to do all N-P tests do (and more) while a member of the Fisherian Tribe (3.3). We consider the frequentist principle of evidence FEV and the divergent interpretations that are called for by Cox’s taxonomy of null hypotheses. The last member of the taxonomy–substantively based null hypotheses–returns us to the opening episode of GTR. Continue reading →

Categories: Severity, Statistical Inference as Severe Testing | 16 Comments

First Look at N-P Methods as Severe Tests: Water plant accident [Exhibit (i) from Excursion 3]

Posted on December 4, 2018 by Mayo

Excursion 3 Exhibit (i)

Exhibit (i) N-P Methods as Severe Tests: First Look (Water Plant Accident)

There’s been an accident at a water plant where our ship is docked, and the cooling system had to be repaired.  It is meant to ensure that the mean temperature of discharged water stays below the temperature that threatens the ecosystem, perhaps not much beyond 150 degrees Fahrenheit. There were 100 water measurements taken at randomly selected times and the sample mean x computed, each with a known standard deviation σ = 10.  When the cooling system is effective, each measurement is like observing X ~ N(150, 102). Because of this variability, we expect different 100-fold water samples to lead to different values of X, but we can deduce its distribution. If each X ~N(μ = 150, 102) then X is also Normal with μ = 150, but the standard deviation of X is only σ/√n = 10/√100 = 1. So X ~ N(μ = 150, 1). Continue reading →

Categories: Error Statistics, Severity, Statistical Inference as Severe Testing | 44 Comments

Neyman-Pearson Tests: An Episode in Anglo-Polish Collaboration: Excerpt from Excursion 3 (3.2)

Posted on December 1, 2018 by Mayo

Neyman & Pearson

3.2 N-P Tests: An Episode in Anglo-Polish Collaboration*

We proceed by setting up a specific hypothesis to test, H0 in Neyman’s and my terminology, the null hypothesis in R. A. Fisher’s . . . in choosing the test, we take into account alternatives to H0 which we believe possible or at any rate consider it most important to be on the look out for . . .Three steps in constructing the test may be defined:

Step 1. We must first specify the set of results . . .

Step 2. We then divide this set by a system of ordered boundaries . . .such that as we pass across one boundary and proceed to the next, we come to a class of results which makes us more and more inclined, on the information available, to reject the hypothesis tested in favour of alternatives which differ from it by increasing amounts.

Step 3. We then, if possible, associate with each contour level the chance that, if H0 is true, a result will occur in random sampling lying beyond that level . . .

In our first papers [in 1928] we suggested that the likelihood ratio criterion, λ, was a very useful one . . . Thus Step 2 proceeded Step 3. In later papers [1933–1938] we started with a fixed value for the chance, ε, of Step 3 . . . However, although the mathematical procedure may put Step 3 before 2, we cannot put this into operation before we have decided, under Step 2, on the guiding principle to be used in choosing the contour system. That is why I have numbered the steps in this order. (Egon Pearson 1947, p. 173)

In addition to Pearson’s 1947 paper, the museum follows his account in “The Neyman–Pearson Story: 1926–34” (Pearson 1970). The subtitle is “Historical Sidelights on an Episode in Anglo-Polish Collaboration”!

We meet Jerzy Neyman at the point he’s sent to have his work sized up by Karl Pearson at University College in 1925/26. Neyman wasn’t that impressed: Continue reading →

Categories: E.S. Pearson, Neyman, Statistical Inference as Severe Testing, statistical tests, Statistics | 1 Comment

Where Are Fisher, Neyman, Pearson in 1919? Opening of Excursion 3

Posted on November 30, 2018 by Mayo

Excursion 3 Statistical Tests and Scientific Inference

Tour I Ingenious and Severe Tests

[T]he impressive thing about [the 1919 tests of Einstein’s theory of gravity] is the risk involved in a prediction of this kind. If observation shows that the predicted effect is definitely absent, then the theory is simply refuted.The theory is incompatible with certain possible results of observation – in fact with results which everybody before Einstein would have expected. This is quite different from the situation I have previously described, [where] . . . it was practically impossible to describe any human behavior that might not be claimed to be a verification of these [psychological] theories. (Popper 1962, p. 36)

Mayo 2018, CUP

The 1919 eclipse experiments opened Popper’ s eyes to what made Einstein’ s theory so different from other revolutionary theories of the day: Einstein was prepared to subject his theory to risky tests.[1] Einstein was eager to galvanize scientists to test his theory of gravity, knowing the solar eclipse was coming up on May 29, 1919. Leading the expedition to test GTR was a perfect opportunity for Sir Arthur Eddington, a devout follower of Einstein as well as a devout Quaker and conscientious objector. Fearing “ a scandal if one of its young stars went to jail as a conscientious objector,” officials at Cambridge argued that Eddington couldn’ t very well be allowed to go off to war when the country needed him to prepare the journey to test Einstein’ s predicted light deflection (Kaku 2005, p. 113). Continue reading →

Categories: SIST, Statistical Inference as Severe Testing | 1 Comment

Stephen Senn: On the level. Why block structure matters and its relevance to Lord’s paradox (Guest Post)

Posted on November 22, 2018 by Mayo

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Stephen Senn
Consultant Statistician
Edinburgh

Introduction

In a previous post I considered Lord’s paradox from the perspective of the ‘Rothamsted School’ and its approach to the analysis of experiments. I now illustrate this in some detail giving an example.

What I shall do

I have simulated data from an experiment in which two diets have been compared in 20 student halls of residence, each diet having been applied to 10 halls. I shall assume that the halls have been randomly allocated the diet and that in each hall 10 students have been randomly chosen to have their weights recorded at the beginning of the academic year and again at the end. Continue reading →

Categories: Lord's paradox, Statistical Inference as Severe Testing, Stephen Senn | 34 Comments

SIST* Posts: Excerpts & Mementos (to Nov 30, 2018)

Posted on November 20, 2018 by Mayo

Surveying SIST Posts so far

SIST* BLOG POSTS (up to Nov 30, 2018)

Excerpts

  • 05/19: The Meaning of My Title: Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars
  • 09/08: Excursion 1 Tour I: Beyond Probabilism and Performance: Severity Requirement (1.1)
  • 09/11: Excursion 1 Tour I (2nd stop): Probabilism, Performance, and Probativeness (1.2)
  • 09/15: Excursion 1 Tour I (3rd stop): The Current State of Play in Statistical Foundations: A View From a Hot-Air Balloon (1.3)
  • 09/29: Excursion 2: Taboos of Induction and Falsification: Tour I (first stop)
  • 10/10: Excursion 2 Tour II (3rd stop): Falsification, Pseudoscience, Induction (2.3)
  • 11/30: Where are Fisher, Neyman, Pearson in 1919? Opening of Excursion 3

Mementos, Keepsakes and Souvenirs

  • 10/29: Tour Guide Mementos (Excursion 1 Tour II of How to Get Beyond the Statistics Wars)
  • 11/8:   Souvenir C: A Severe Tester’s Translation Guide (Excursion 1 Tour II)
  • 10/5:  “It should never be true, though it is still often said, that the conclusions are no more accurate than the data on which they are based” (Keepsake by Fisher, 2.1)
  • 11/14: Tour Guide Mementos and Quiz 2.1 (Excursion 2 Tour I Induction and Confirmation)
  • 11/17: Mementos for Excursion 2 Tour II Falsification, Pseudoscience, Induction

*Statistical Inference as Severe Testing: How to Get Beyond the Statistics Wars (Mayo, CUP 2018)

Categories: SIST, Statistical Inference as Severe Testing | 3 Comments

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