Rate how well the engagement absorbs model version deprecations and retirements forced by model providers

The mean rating was 4.6 and the median 5.0 (n = 793 respondents). Ratings of 3 or below, the distressed range, made up 32.16% of the answers. The rating was associated with all four study measures. Higher ratings came with less cancellation (r = −0.64, 95% CI −0.72 to −0.53, p < 0.001, n = 150 engagements), higher customer satisfaction among active engagements (r = 0.71, 95% CI 0.59 to 0.80, p < 0.001, n = 94 engagements), a higher engagement indicator mean computed without the indicator (r = 0.87, 95% CI 0.83 to 0.91, p < 0.001, n = 150 engagements) and lower intent to leave (r = −0.66, cluster bootstrap 95% CI −0.72 to −0.60, p < 0.001 with standard errors clustered by engagement, n = 748 respondents). After Holm correction, ratings differed by engagement status and lifecycle stage (Welch F 37.76, Holm p < 0.001, omega squared 0.396) and respondent role (Welch F 7.15, Holm p = 0.009, omega squared 0.015).

All 39 written responses came from C198, the comment field on the third-party ecosystem. Twenty-four were negative and fifteen positive. The accounts divided on notice and preparation: engagements that had a month's notice and a way to compare old and new versions absorbed retirements without breakage, while those with short notice, no second model and no list of what depended on the old version lost days of work. No written outcome test reached significance.

Ratings of 3 or below, the distressed range, accounted for 255 of the 793 answers (32.16%). The engagement mean fell in the distressed range in 37 of 150 engagements.

The primary responses numbered 39, all written in answer to C198, “Add any comments on the third-party ecosystem that the ratings in this section do not capture.” No response from any other question addressed the indicator, so every response was primary.

Nine responses described time lost or work redone after a model version was retired: a content template rebuilt in two days, prompts rebuilt over a lost week and two Saturdays, cheat sheets redone at every change, an endorsement queue that sat for two days in the middle of a cycle, and tax memos that came back with their headings gone because notice reached the team in the week of the change. Three said no one knew which templates or rules depended on the old version or who would re-test them, and one team went through every valuation template by hand for a week. Six said there was no second model ready, one asking for a second model kept warm and tested against the team's own cases rather than a paragraph in a continuity plan.

Eleven responses said a retirement was absorbed without breakage, typically with two weeks' to a month's notice, and one said nobody on the team even noticed. Three described a simple safeguard: the old prompt set run against the new version for a day, or last month's output kept to compare before anything went out. One respondent said the comparison took twenty minutes and had caught two or three problems. Several responses on both sides raised licenses written per named user. Such licenses did not fit an agent, and one respondent said the question had to be resolved before the next retirement.

Of the 39 responses, 24 (61.54%, 95% CI 45.71% to 76.32%) were negative and 7 (17.95%) carried the strongest negative score of −10. Positive responses numbered 15 (38.46%), and no response was neutral. The mean written score was −1.5 (95% CI −3.7 to 0.6, n = 39 responses), and the median was −5.0.

Of the 39 responses, 38 came from respondents who also rated the indicator. Among them, the written score rose with the rating (Spearman rho 0.65, 95% CI 0.43 to 0.81, p < 0.001, n = 38 responses). The written responses corroborated the rating. Of the 23 negative responses with a rating, 11 (47.83%) came from respondents whose rating was in the distressed range.

Respondents who wrote about the indicator and gave a rating numbered 38, with a mean rating of 5.1. The 755 respondents who rated the indicator without writing about it had a mean of 4.6. The difference, 0.5 (95% CI −0.4 to 1.4), included zero. Ratings in the distressed range made up 28.95% of the ratings from respondents who wrote (11 of 38) and 32.32% of the ratings from respondents who did not (244 of 755).

Every figure in the segment tables is at respondent level. Segments with fewer than 30 respondents carry no interval. Segments with fewer than 10 report counts only.

Segment families recorded at engagement level were tested on engagement means. Respondent role and vendor type were tested on respondents. Where an expected count fell below 5, the test of the distressed share used Fisher's exact test for a two-by-two table, marked exact, or a Monte Carlo test, marked simulated. After Holm correction, ratings differed by engagement status and lifecycle stage (Welch F 37.76, Holm p < 0.001, omega squared 0.396). Active engagements in Production rated highest (mean 5.7, n = 98 respondents) and canceled engagements lowest (mean 3.1, n = 299 respondents). Ratings also differed by respondent role (Welch F 7.15, Holm p = 0.009, omega squared 0.015). Portfolio directors rated highest (mean 5.8, n = 31 respondents) and individual contributors lowest (mean 4.5, n = 610 respondents). Outsourcing model, institution type, process family, class of work and vendor type showed no difference.

Written sentiment did not differ by engagement status and lifecycle stage across the 33 engagements with a written response (Kruskal-Wallis H 2.29, df 3, p = 0.515). Of the groups with 10 or more responses, responses from active engagements in Transition/Cut-Over were the most negative (mean −3.5, 10 responses) and responses from canceled engagements the least negative (mean −1.3, 15 responses). Responses from active engagements in Build-Out (6) and active engagements in Production (8) are reported as counts only.

No test across respondent roles was run, because fewer than two roles had 30 or more written responses. Individual contributors wrote 22, engagement managers wrote 12 and portfolio directors wrote 5 responses, reported as counts only.

Cancellation rate is the share of engagements canceled by the study date, measured at engagement level (150 engagements, 56 canceled). Canceled engagements were rated after cancellation. The association is therefore a descriptive contrast and not a forecast of cancellation.

Across the study set, higher ratings came with less cancellation (r = −0.64, 95% CI −0.72 to −0.53, Holm p < 0.001, n = 150 engagements). The association held after Holm correction in thirteen of the 20 segment levels tested.

Customer satisfaction is the percentage recorded against each engagement. The primary estimate uses the 94 active engagements. A descriptive contrast uses all 150 engagements.

Across the active engagements, higher ratings came with higher customer satisfaction (r = 0.71, 95% CI 0.59 to 0.80, Holm p < 0.001, n = 94 engagements). The association held after Holm correction in fourteen of the 16 segment levels tested.

The engagement indicator mean is the mean of an engagement's ratings across the rated indicators, measured at engagement level (150 engagements). The indicator is one of the rated indicators. Each comparison therefore uses the mean recomputed without it.

Higher ratings came with a higher engagement indicator mean (r = 0.87, 95% CI 0.83 to 0.91, Holm p < 0.001, n = 150 engagements). The association held after Holm correction in twenty-four of the 24 segment levels tested.

Intent to leave is the answer to C019, “How likely are you to leave your current job in the next 12 months?”, rated 1 to 10. It is measured at respondent level on up to 798 respondents, with the engagement-level form reported alongside.

Respondents who gave higher ratings reported lower intent to leave (r = −0.66, 95% CI −0.70 to −0.62, Holm p < 0.001, n = 748 respondents). The association held after Holm correction in thirty-six of the 37 segment levels tested.

Two comparisons set the engagements with at least one negative response against all other engagements. Of the 129 other engagements, 117 had no written response addressing the indicator. These two comparisons therefore do not isolate written sentiment. Of the 21 engagements with a negative response, 8 (38.10%) were canceled, against 48 of the 129 other engagements (37.21%). The difference did not reach significance (Fisher exact p = 1.000). Customer satisfaction among active engagements did not differ between the two groups (mean 69.46% on 13 engagements against 63.23% on 81, Welch t 1.76, p = 0.098).

Two correlations test written sentiment directly. Across the 33 engagements with a written response, the engagement mean written score was not associated with cancellation (point-biserial r 0.08, p = 0.666). Across 37 respondents, the respondent mean written score was not associated with intent to leave (Spearman rho −0.12, p = 0.464). Of the four comparisons, none reached significance at 0.05.

The four associations were compared in pairs on their engagement-level forms, each oriented so that a higher value is the better outcome, across the 150 engagements with all four measures. After Holm correction, five of the six pairs differed. The association with the engagement indicator mean was the strongest and the association with cancellation the weakest. The associations with customer satisfaction and intent to leave did not differ (Holm p = 0.418).

Answers clustered within engagements (ICC 0.63). Clustering reduced the 793 respondent answers to the equivalent of about 214 independent answers. Respondent-level intervals therefore used the cluster bootstrap. Respondent-level tests of intent to leave used standard errors that allow for clustering by engagement.

No association was equivalent to zero. Each of the four differed from zero. The detection floor shown is the study floor at 150 engagements. Intent to leave was tested on its effective sample size.

Each change was computed before rounding and may differ by 0.01 from the difference between the two printed values.

All 22 checks held. A check holds when its test falls on the same side of 0.05 as the primary test. Where the primary test falls below 0.05, the check must also keep the sign of the primary correlation. The thin-base check removes the engagements in any level of outsourcing model or process family with fewer than 30 engagements. Institution type is not used for that check, because every one of its levels has fewer than 30 engagements.

Each of the four measures was computed from data the indicator does not contain. Each result is therefore a finding and not an arithmetic consequence. The indicator is one of the rated indicators, and the engagement indicator mean was recomputed without it. The correction changed r by 0.00, from 0.88 to 0.87.

Each deviation was computed before rounding and may differ by 0.01 from the difference between the two printed values.

The comparison covered 150 engagements. The indicator followed the study's typical pattern on all four measures, and no deviation held after Holm correction.

Among the 71 Part 2 indicators with 30 or more written responses, the indicator's share of negative responses, 61.54%, ranked 68th from the highest, against a median of 80.82%. Its mean written score, −1.5, ranked 70th from the most negative, against a median of −4.7.

The indicator most often present in the same responses was C181, “Rate the quality of advance notice third-party providers give before changes that can affect the agents on this engagement.”, in 24 of the 39 responses (61.54%). C178, “Rate how well the agents on this engagement are protected from breaking silently when a third party changes something without warning.” (7 responses), C179, “Rate the quality of the fallback the engagement has ready when a critical third-party feed, platform, or model stops working.” (7 responses), C196, “Rate how completely the engagement has mapped every third and fourth party its agents depend on, down the full chain.” (7 responses) and C182, “Rate how reliably word of an upcoming third-party change reaches the people who operate the affected agents in time to act.” (6 responses) followed.

The most frequent theme was “Detection only by failure”, in 9 responses (23.08%). The second was “Comparison to a prior engagement”, in 4 responses.

About a third of all ratings of how well the engagement absorbed model version retirements fell in the distressed range (255 of 793 answers, 32.16%). The rating was associated with all four study measures, and every association held under each of the 22 robustness checks. Canceled engagements rated far below the three active stages (mean 3.1, n = 299 respondents).

The written evidence presents model retirement as a recurring and predictable event whose cost depended on preparation. A dependency list, a side-by-side comparison and a second model turned it into a routine switch, and their absence turned it into days of lost work. For a financial institution, that loss can fall in the week of a filing deadline.

The evidence is the reported experience of the vendor's delivery teams, collected in a single cross-section. The associations reported here are not causal.

Tests by respondent role and by vendor type treated respondents as independent. The section on clustering reports how far clustering within engagements reduced the information in respondent-level figures.

Customer management executives gave 2 answers, a base of anecdote strength.

Shares of written sentiment are shares of responses and not of the study set of respondents. The written score takes five fixed values, so its mean and median are coarse. Responses clustered within engagements (39 responses on 33 engagements). Intervals for written sentiment therefore used a bootstrap by engagement.